THREE ESSAYS ON SUBJECTIVE WELLBEING
KUSHNEEL AVNEET PRAKASH
B.Com, PG.Dip[Econs], M.Com[Econs]
The University of the South Pacific
A thesis submitted for the degree of Doctor of Philosophy at
Monash University in 2020
Department of Economics
i
Copyright Notice
© The author (2020).
I certify that I have made all reasonable efforts to secure copyright permissions for
third-party content included in this thesis and have not knowingly added copyright
content to my work without the owner's permission.
ii
Abstract
This dissertation is a collection of three distinct, but related, papers on subjective
wellbeing (SWB). Economists are increasingly turning their attention to shining a light
on what determines how satisfied people are with their lives and why some people are
more satisfied with their lives than others. Chapter 1 presents a brief introduction on
the concept of SWB in general and outlines a brief summary of the three related studies
on SWB.
The first paper, ‘The Quintessential Chinese Dream’? Homeownership and the
Subjective Wellbeing of China’s Next Generation examines how homeownership
influences the SWB of children. Specifically, this chapter utilises nationally
representative panel data from China Family Panel Studies to examine how parental
homeownership status influences the subjective wellbeing of their children in China.
The results show that children aged 10-15 years of homeowners have 2.79 percentage
points higher subjective wellbeing than children of non-homeowners. This finding
continues to hold after using a series of alternative approaches to address the
endogeneity of homeownership status and a number of other robustness checks. The
results also suggest that parental inputs into their children’s education, investment in
home maintenance, the quality of the neighbourhood and parents’ emotional support
for their children are channels through which homeownership influences children’s
subjective wellbeing.
The second paper, Housing Wealth and Happiness in Urban China contributes to the
discourse regarding rapid growth in inequality in housing wealth in China. This
chapter examines how housing wealth and housing wealth inequality are associated
with happiness, drawing on panel data from China Household Finance Survey. I find
that housing wealth and housing wealth inequality matter for happiness and that more
housing wealth increases happiness with diminishing returns to owning a second and
third house. The results also show that the relationship between housing wealth
inequality and happiness depends on one’s reference group and the level of housing
wealth inequality. I also employ the concentration index to examine the effect of
housing wealth inequality on happiness inequality. The wealth-related concentration
iii
index for happiness are all positive, suggesting that higher happiness is more
concentrated among people with higher housing wealth.
Finally, in the third paper, Petrol Prices and Subjective Wellbeing I examine the effect
of petrol prices on SWB using household panel data. To do so, I use 17 waves of the
Household, Income and Labour Dynamics in Australia (HILDA) survey. Based on our
preferred instrumental variable estimates, we find that a standard deviation increase in
petrol prices leads to a decline of 0.0157–0.0245 standard deviations in SWB. The
finding that increases in petrol prices significantly lower SWB is robust to alternative
measures of wellbeing and alternative ways of addressing endogeneity, as well as
employing different sources of fuel price data measured at a range of frequencies. We
also examine the channels through which petrol prices influence SWB and find that
maintaining social networks is an important way through which petrol prices influence
SWB.
iv
Declaration
This thesis is an original work of my research and contains no material which has been
accepted for the award of any other degree or diploma at any university or equivalent
institution and that, to the best of my knowledge and belief, this thesis contains no
material previously published or written by another person, except where due
reference is made in the text of the thesis.
Print Name:
Kushneel Avneet Prakash
Date:
29/09/2020
v
Publications during enrolment
1. Locus of control and the gender gap in mental health. Journal of Economic
Behavior & Organization, 2020, 178, 740-758 (with R. Smyth, S. Awaworyi
Churchill, M. Munyanyi). [Not part of thesis]
2. Petrol prices and subjective wellbeing. Energy Economics, 90 [104867] (with
R. Smyth, S. Awaworyi Churchill). [Part of thesis]
3. Housing wealth and happiness in urban China. Cities, 2020, 96 [102470] (with
R. Smyth, Z. Cheng, H. Wang). [Part of thesis]
4. ‘The quintessential Chinese dream’? Homeownership and the subjective
wellbeing of China’s next generation. China Economic Review, 2019, 58
[101350] (with R. Smyth). [Part of thesis]
vi
Thesis including published works declaration
I hereby declare that this thesis contains no material which has been accepted for the
award of any other degree or diploma at any university or equivalent institution and
that, to the best of my knowledge and belief, this thesis contains no material previously
published or written by another person, except where due reference is made in the text
of the thesis.
This thesis includes three original papers published in peer reviewed journals. The core
theme of the thesis is subjective wellbeing. The ideas, development and writing up of
all the papers in the thesis were the principal responsibility of myself, the student,
working within the Department of Economics under the supervision of Prof. Russell
Smyth.
The inclusion of co-authors reflects the fact that the work came from active
collaboration between researchers and acknowledges input into team-based research.
In the case of each respective chapters containing published works, my contribution to
the work involved the following:
Thesis
Chapter
Publication Title Status
Nature and %
of student
contribution
Co-author name(s)
CoNature and % of Coauthor(s),
author’s contribution* Monash
student
1. Russell Smyth
No
- input into manuscript
[20%]
Two
‘The quintessential
Chinese dream’?
Homeownership
and the subjective
wellbeing of
China’s next
generation
Published
Concept,
collecting data,
data analysis
and writing first
draft [80%]
Three
Housing wealth
and happiness in
urban China
Published
Concept,
1. Russell Smyth
collecting data,
- input into manuscript
data analysis
[10%]
and writing first
2. Zhiming Cheng
draft [50%]
- input into manuscript
[20%]
3. Haning Wang
- input into manuscript
[20%]
vii
No
No
No
Four
Petrol prices and
subjective
wellbeing
Published
Concept,
1. Russell Smyth
collecting data,
- input into manuscript
data analysis
[10%]
and writing first
2. Sefa Awaworyi
draft [70%]
Churchill
- input into manuscript
[20%]
No
No
I have renumbered sections of published papers in order to generate a consistent
presentation within the thesis.
Student name:
Kushneel Avneet Prakash
Date:
29/09/2020
I hereby certify that the above declaration correctly reflects the nature and extent of
the student’s and co-authors’ contributions to this work. In instances where I am not
the responsible author I have consulted with the responsible author to agree on the
respective contributions of the authors.
Main Supervisor name:
Prof. Russell Smyth
Date:
29/09/2020
viii
Dedication
This thesis is dedicated to my mummy and papa (my beloved parents):
Mr. Satendra Prakash and Mrs. Arun Lata Prakash
&
to my be-all and end-all lovely wife, Reema.
ix
Acknowledgements
My first and foremost heartfelt appreciation goes out to my awesome main supervisor,
Prof. Russell Smyth. Russell, my mentor, deserves the most credit for taking me under
his wings. He didn’t have to, and for that I am for ever thankful. Russell has not only
helped me frame my research ideas, but he has been super inspirational and supportive
at every step in my PhD journey. He allowed me to come out of my comfort zone to
learn new software and explore research questions using survey data on things which
matter for wellbeing. Most important of all, he gave me enough space and support to
make me an independent researcher. From the time I was exploring my PhD options
at Monash University, I have always adored his intellect, work ethics, professionalism
and his amiable personality. While he would have new publications coming in almost
every month with many more in revise and resubmit form with his co-authors and
other students, his detailed feedback with very quick turn around on my work would
make me feel that I am probably his only student. He is just amazing.
I fondly recollect all the stimulating discussions I had with Russell in his office at
Clayton and Caulfield campus and at times over lunch, which he would graciously pay
for. He would encourage me to make the most of my time as a PhD student by
attending and/or presenting at relevant local and international PhD conferences and
workshops. He made me realise that this PhD is a journey rather than a destination in
itself. On a much brighter personal note, while some of my PhD mates would go
paranoid seeing their supervisor, bumping into Russell either in Menzies corridor or
in the tea room would always lead to pleasant conversations ranging from studies,
weekend sports, recommendations for travelling on business class on my next trip
abroad to suggestions for having expensive coffee with scenic view during afternoon
twilight on the hills of Florence in Italy (which I did but with a glass of wine). I could
not have imagined having a better mentor for my PhD who gave me the same level of
respect he would give to any of his co-authors and his colleagues. I hope to continue
with the collegial bond we have created and continue working together on new
research ideas and publications for many more years to come.
I am also indebted to all those who have commented on my three PhD papers. The
comments and suggestion from my PhD panel committee members, Prof. Lata
x
Gangadharan, Dr. Vinod Mishra and Dr. Liang Choon Wang had allowed me to better
frame my research questions and improve on the analysis for the robustness of the
results. I truly appreciate their time in reading my work and their honest feedback and
their desire for me to do well. I would also like to extend my sincere gratitude to those
with whom I have had discussions with or have commented on my work. I found
renowned economists at academic conferences incredibly supportive where people
were genuinely willing to give valuable feedback to PhD students. With apologies in
advance for inevitably forgetting someone, I express my sincere gratitude to Dr.
Haining Wang from Sun Yat-sen University, Dr. Zhiming Cheng from University of
New South Wales, Dr. Sefa Awaworyi Churchill from RMIT University, Dr. Habibur
Rahman from Monash University Malaysia campus, Prof. Kenneth Clements from
University of Western Australia, Prof. Mark Wooden from University of Melbourne,
and the anonymous reviewers from the China Economic Review, Cities and Energy
Economics journal plus the many people who have sat through my presentations and
commented on my work either orally or via emails. Their comments and advice have
guided and challenged my thinking to improve the analysis and arguments in my
papers to a publishable quality. In particular, I would like to convey my sincere
gratitude to Dr. Sefa who taught me a lot on the art of publishing and included me as
part of a number collaborations that we are currently working on. Special thanks also
to my two thesis examiners who have provided useful insights and suggestions for
future work.
I was also blessed to have a great cohort of like-thinking minds doing PhD with whom
I have often discussed my research ideas, shared casual drinks or played futsal. In no
particular order, I thank Justin, Ratul, Veasna, Chau, Leo, Lizzy, Main, Ola, Abby,
Hasib, Lina, Ben and Abebe for the company and collegial support throughout my
journey. At this point I would also like to acknowledge the financial support of our
department and Monash Graduate Association (MGA) to our PhD society which I was
coordinating with Ratul to organise team bonding activities for our group. I would also
like to thank all the academic and professional staff at the Department of Economics
of Monash University who all made me feel part of the department and provided me
with a decent workstation for working on campus and to work from home during the
COVID-19 pandemic situation.
xi
I would also like to extend my sincere appreciation to the Monash University for
awarding me with scholarships to cover for my tuition fees via Monash International
Postgraduate Research Scholarship (MIPRS) and Monash Graduate Scholarship
(MGS) to cover for my stipend. Special mention also goes out to the Department of
Economics for awarding me with departmental top-up scholarship, which provided
additional stipend during my study years.
Most importantly, I thank my mum and dad for their unconditional support and
motivation during the course of my program. It is fair to say that attaining PhD and
having academic title Dr. in front of my name was my parents’ dream which overtime
became my drive to do well at school and universities I attended. The passion to excel
and make my parents proud has defined me and my career choices, for which I am
forever grateful.
Special acknowledgment also goes out to my friends and brother back at home. To
Ronil, my little brother, thank you so much for late night chats which would refresh
my mind from the constant thoughts on my work. Thank you for taking the burden of
managing the construction our family home back in Fiji when I came over to
Melbourne for studies. This was a huge relief that allowed me to focus fully on my
studies knowing that you took the responsibilities on your shoulders as a strong and
responsible man you have grown to be. Thanks to also my friends who have become
more like my family, namely Krishneel, Jaynesh, Ashneel, Sanjesh, Preetika, Ashna,
Ashley, Kelvin, Edwin, Namita and young Neytik for constantly being in contact and
making me feel closer to home always.
And finally, to my better-half, my lovely wife, Reema. I am lucky and blessed to have
her beside me in this journey of ours. Her moral support, love, warmth, laughter and
adventures made this a fun and exciting journey. I thank her for all the understanding
and patience in moving to a new city right after our wedding and making our small
rental apartment, a home. She is the one where I would find comfort at the end of tiring
day, weeks, months and years. I couldn’t have imagined a better person to share this
success and achievements besides her. For that, I am eternally grateful. You are, and
forever will be, my be-all and end-all.
xii
TABLE OF CONTENTS
CHAPTER 1
INTRODUCTION
1-8
CHAPTER 2
‘THE QUINTESSENTIAL CHINESE
DREAM’? HOMEOWNERSHIP AND THE
SUBJECTIVE WELLBEING OF CHINA’S
NEXT GENERATION
9-58
Abstract
10
Section 2.1
Introduction
11
Section 2.2
Conceptual framework and channels
14
Section 2.3
China’s context
16
Section 2.4
Data
18
Section 2.5
The Empirical Model
24
Section 2.6
Empirical Results
28
Section 2.7
Extensions and robustness checks
35
Section 2.8
Conclusion
41
References
44
Appendices
51
CHAPTER 3
HOUSING WEALTH AND HAPPINESS IN
URBAN CHINA
59-93
Abstract
60
Section 3.1
Introduction
61
Section 3.2
Literature Review
63
Section 3.3
How does housing wealth of others affect
happiness in Chinese cities?
65
Section 3.4
Data and methods
67
Section 3.5
Main results
73
Section 3.6
Robustness checks
78
Section 3.7
Conclusion
82
References
84
Appendices
90
CHAPTER 4
Section 4.1
PETROL PRICES AND SUBJECTIVE
WELLBEING
94-161
Abstract
95
Introduction
96
xiii
Section 4.2
Why should petrol prices influence subjective
wellbeing?
Section 4.3
Data and Variables
101
103-108
Section 4.3.1
Main outcome variable
104
Section 4.3.2
Petrol prices
107
Section 4.3.3
Covariates
108
Section 4.3.4
Channels
108
Section 4.4
Empirical Method
109
Section 4.5
Results
115-136
Section 4.5.1
Baseline results
115
Section 4.5.2
Addressing endogeneity
117
Section 4.5.3
Potential channels through which petrol prices
influence SWB
117
Section 4.5.4
Extension and robustness checks
121-137
Section 4.5.4.1 Heterogenous effects across sub–groups
121
Section 4.5.4.2 Role of volatility and lagged effects of petrol price
on SWB
124
Section 4.5.4.3 Economic significance of petrol price effects
128
Section 4.5.4.4 Employing alternative IVs
130
Section 4.5.4.5 Alternative measures of wellbeing
131
Section 4.5.4.6 Robustness to alternative fuel data and other
sensitivity checks
134
Section 4.6
Conclusion
137
References
140
Appendices
150
CHAPTER 5
CONCLUSION
162-165
APPENDICES
Chapter 2 published paper
Chapter 3 published paper
xiv
List of Tables
2.1
Descriptive Statistics
23
2.2
Determinants of subjective wellbeing for children, CFPS (OLS
results)
29
2.3
Determinants of subjective wellbeing in sub-samples, CFPS (OLS
results)
31
2.4
Structural equation model of the relationship between
homeownership and subjective wellbeing
33
2.5
Robustness checks (instrumenting endogenous variables)
36
2.6
Propensity score matching estimates of the average treatment
effects of homeownership on subjective wellbeing of children,
CFPS
38
2.7
Robustness checks, CFPS (4 waves – 2010-2012-2014-2016)
39
2.8
Robustness checks, CFPS (same children surveyed over 20102012-2014 waves)
40
3.1
Summary statistics of key variables, China Household Finance
Survey 2011-2015
71
3.2
Fixed effects estimates of housing wealth and housing wealth
inequality on happiness
74
3.3
Fixed effects estimates
76
3.4
Decomposition of the concentration index of happiness
78
3.5
Robustness check: coefficient stability
79
3.6
Robustness check: fixed effects estimates with different
specifications
80
4.1
Subjective wellbeing by various categories
106
4.2
Petrol prices and subjective wellbeing, using city-level monthly
ULP price data (baseline results)
118
4.3
Petrol prices and subjective wellbeing, using city-level monthly
ULP price data (IV results)
119
4.4
Estimated indirect and direct effects of petrol prices on subjective
wellbeing
120
4.5
Lagged petrol prices, petrol price volatility and subjective
wellbeing
126
4.6
The income equivalence of rising petrol prices
129
4.7
Robustness checks: employing alternative IVs
131
4.8
Robustness checks: alternative measures of wellbeing
133
4.9
Robustness check: Petrol prices and subjective wellbeing using
city-level monthly diesel price data (IV results)
135
xv
List of Figures
2.1
Diagrammatic representation of home tenure status in the total
sample
21
2.2
Subjective wellbeing by categories of homeownership
22
3.1
Housing wealth inequality by province in 2015
62
3.2
Concentration curve for housing wealth-related happiness
72
4.1
Trends in life satisfaction in sample over time: HILDA waves 1-17
105
4.2
Heterogeneous effects of petrol price on life satisfaction by subgroups
122
xvi
List of Appendices
A2.1
Factor analysis for the subjective wellbeing items
51
A2.2
Definition of variables
52
A2.3
Determinants of subjective wellbeing for children, CFPS (ordered
logit & ordered probit model results)
56
A2.4
Determinants of subjective wellbeing in sub-samples, CFPS (IV
results)
57
A2.5
Factor analysis for the subjective wellbeing items (as used in
robustness tests)
58
A3.1
Summary statistics, China Household Finance Survey 2011, 2013
and 2015
90
A3.2
Decomposition of Gini coefficient by source of housing wealth
(full sample)
91
A3.3
Fixed effects estimates of housing wealth inequality within
different reference groups on happiness
92
A3.4
Housing wealth, non-housing wealth and happiness
93
A4.1
Description and Summary Statistics of variables
150
A4.2
Test on the validity of IV
152
A4.3
Petrol prices and Life satisfaction, full baseline and 2SLS results
153
A4.4
Petrol prices and subjective wellbeing, alternating years
155
A4.5
Petrol prices and subjective wellbeing, using state-level yearly
petrol prices
156
A4.6
Petrol prices and subjective wellbeing, heterogeneous effects by
geographical location and vehicle ownership using state-level
yearly petrol prices
157
A4.7
Petrol prices and subjective wellbeing using alternative yearly fuel
prices (IV results)
158
A4.8
Petrol prices and subjective wellbeing, clustering at city-level
159
A4.9
Petrol prices and subjective wellbeing, using equivalized income
160
A4.10
Baseline and 2SLS results, using average monthly temperature as
an additional control variable
161
xvii
CHAPTER 1
INTRODUCTION
1
There has been a remarkable surge in interest in studying life satisfaction, happiness,
or the more precise term in the economics literature, “subjective wellbeing” (SWB)
over the past two decades. Surveys based on answers to the question “how satisfied
are you with your life?” have provided scholars and policy makers alike increased
understanding of the factors influencing perceived happiness. The notion that
formulation of public policy by policy makers should aim for something beyond the
traditional measures of GDP is far from new, but it has gained prominence in recent
times. The Stiglitz Commission (Stiglitz, Sen & Fitoussi, 2009), for instance,
recommended the use of subjective measures, such as SWB, to measure, and monitor,
social progress. There is now growing interest among policymakers in using measures
of SWB to evaluate the impact of policy (see eg. DiMaria, Peroni & Sarrccino, 2019;
Sachs, Becchetti & Annet, 2016). Improving SWB has, thus, become an important
policy objective in many countries. The focus on Gross National Happiness as the goal
of the government in Bhutan since 2008 and the recent 2019 Wellbeing Budget in New
Zealand are a few examples of its growing importance. Economists are, thus,
increasingly turning their attention to understanding what determines how satisfied
people are with their lives and why some people are more satisfied with their lives than
others. There are some correlates with SWB that are well-known (see Coates, Anand
& Norris (2013) and Dolan, Peasgood & White (2008) for recent reviews), but much
is still to be learnt. This dissertation contributes to our understanding of the factors
correlated with SWB through the presentation of three independent essays.
The first paper of this dissertation focusses on the effect of one of the important
objectives for many people in their life, owning one’s own home. Numerous studies
have shown that owning one’s own home is linked to many economic and social
benefits for family members and the society at large.1 The role of homeownership has
not only received attention in the economics discipline, but it has been examined from
a multi-disciplinary approach. Scholars have discussed, and analysed, the
consequences of homeownership from various perspective including demography,
economics, geography, political science, psychology and sociology. 2 While there are
studies on the economic and social implications of homeownership on homeowners
1
See Dietz and Haurin (2003) and Rohe, Zandt and McCarthy (2002) for discussion on various social
and economic effects of homeownership.
2
See Zavisca and Theodore (2016) for a recent review.
2
and their children, the effect of homeownership on children’s SWB has received very
little attention in the literature. There is only one study that includes homeownership
status as one of the variables in a general study of the SWB of children in the UK. The
novel contribution of my first paper is that I present the first study to examine in depth
the relationship between homeownership and SWB of children. I also use panel data
rather than cross-sectional data and address endogeneity of homeownership together
with examining the channels via which homeownership may affect SWB of children.
To do so, I focus on China and employ nationally representative longitudinal data for
that country from the China Family Panel Studies (CFPS) survey.
China represents a noteworthy case in which to situate a study on the relationship
between homeownership and SWB of children. Homeownership for years was
regarded as the quintessential American dream, but it is now the quintessential Chinese
dream (Sito & Liu, 2018). China is becoming a nation of homeowners, with around
90% of households owning their own homes (Trading Economics, 2018). The Chinese
case allows us to focus on a country outside of the United States or Western Europe in
which much of the literature on the implications of homeownership is concentrated.
This is particularly important because much of the literature on the effects of home
ownership post the Global Financial Crisis in United States or Western European
settings has focused on implications of declining home ownership, while China has
experienced increasing rates of home ownership and now has one of the highest rates
of home ownership in the world.
The findings suggest that parental homeownership status has a positive and significant
effect on the SWB of their children. The channels through which homeownership
influences children’s SWB are found to be parental inputs into their children’s
education, investment in home maintenance, the quality of the neighbourhood and
parents’ emotional support for their children. These findings have considerable policy
relevance given the significant increase in homeownership in China in recent years.
In the second paper of this dissertation, I continue to explore further aspects of housing
and wellbeing in China. China presents an excellent example of a society in which
housing markets were traditionally not important, but the commodification of housing
and the consequential rapid growth in homeownership rates has resulted in
3
unprecedented levels of housing assets in China. Total housing wealth accounts for
nearly 80% per cent of total household wealth which is much higher than in most other
countries (Xie & Jin, 2015). As a result, over the last three decades increasing housing
wealth as a component of total household wealth in China has created massive housing
wealth inequality. The recent work by Piketty (2014) has put an academic spotlight on
the role that inequality in housing wealth has played in contributing to steadily rising
wealth inequality in many economies since the 1970s. While there is growing
international interest in housing wealth inequality as a contributor to overall wealth
inequality there are no existing studies for China, or other countries, that examine how
housing wealth inequality affect happiness using longitudinal data.
In my second paper, I examine how housing wealth and inequality in housing wealth
affects people’s happiness in China using the China Household Finance Survey
(CHFS) data. More specifically, in this paper I am interested in investigating whether
housing wealth inequality contributes to differences in individual happiness in
societies. I also further investigate whether there is increasing returns to happiness for
owning more than one home. The findings show that housing wealth and housing
wealth inequality matter for SWB. The relationship between housing wealth inequality
and SWB depends on the reference group and the level of housing wealth inequality.
I find that more housing wealth increases SWB but with diminishing returns to owning
a second and third house and that higher happiness in China is more concentrated
among people with more housing wealth. At a time when China has experienced rapid
growth in inequality in housing wealth, this study has considerable policy relevance
and calls for increased efforts to reduce general inequality in housing wealth.
In the third paper, I examine the effect of movements in petrol prices on SWB. Since
the first oil price shock of the 1970s, economists have spent a lot of time better
understanding the implications and dynamics of movements in petrol prices (see eg.
Bachmeier & Griffin, 2003; Honarvar, 2009 and Valadkhani, 2013). An implicit
motivation for such studies is that petrol price increases, as well as volatility in petrol
prices, have adverse welfare effects on consumers and that through improving our
understanding of petrol price movements we can reduce harmful welfare effects.
Therefore, a natural extension of such studies, particularly given economists’ parallel
4
keen interest in the antecedents of SWB at the individual level, is to directly examine
how petrol price movements affect SWB.
In examining the relationship between petrol prices and SWB, I employ longitudinal
data from the Household, Income and Labour Dynamics in Australia (HILDA) survey.
Australia is representative of many developed countries that are heavily reliant on
imported petroleum because of rising and highly volatile nature of petrol prices. BoydSwan and Herbst (2012) and Graham and Chattopadhyay (2010) are at least two
studies which have investigated the relationship between fuel prices and wellbeing at
household level. I differ from these studies in several important ways. The first is that
I provide some firm evidence on the relationship between petrol prices and SWB for
a country other than the United States that has experienced rising petrol prices that one
would expect to effect SWB. Second, I differ methodologically from existing studies
and use panel data to address the endogeneity of petrol prices. I also extend my analysis
to examine several channels through which petrol prices potentially influences a
person’s SWB. The empirical findings suggest that increase in petrol prices are
associated with a decline in SWB which remains robust to alternative ways of
addressing endogeneity and to using different fuel prices from different sources and at
different frequencies. Further results show that maintaining social networks is an
important channel through which petrol prices have an adverse effect on SWB. I
further carry out analysis on income equivalence for a change in SWB due to a change
in petrol prices to quantify additional income compensatory effects to maintain the
same level of SWB. Given that there are adverse effects of both diesel and petrol
prices, as well as their volatility, on the wellbeing of individuals, an important policy
implication of this study is to subsidise alternatives to fuel cars and renews calls for
greater investment in public transport services, cycling and walking infrastructure in
Australia. These policy interventions would provide alternatives to travel by car and
reduce the sensitivity of individual SWB to petrol prices.
This dissertation is organised in five chapters. Following this introductory chapter, the
relationship between homeownership and SWB of children in China is explored in
Chapter 2. Chapter 3 extends our understanding on the dynamics of SWB in respect to
housing. In this chapter, the relationship of housing wealth and housing wealth
5
inequality to individual SWB is investigated. Chapter 4 presents the analysis on the
association of the dynamics of petrol prices on SWB. The final Chapter 5, concludes.
6
References
Bachmeier, L., & Griffin, J. (2003). New evidence on asymmetric gasoline price
responses. The Review of Economics and Statistics, 85(3), 772-776.
Boyd-Swan, C., & Herbst, C. (2012). Pain at the pump: Gasoline prices and subjective
well-being. Journal of Urban Economics, 72, 160-175.
Coates, D., Anand, P., & Norris, M. (2013). Housing, happiness and capabilities: A
summary of the international evidence and models. International Journal of
Energy, Environment, and Economics, 21(3), 181-214.
Dietz, R., & Haurin, D. (2003). The social and private micro-level consequences of
homeownership. Journal of Urban Economies, 54, 401-450.
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347-367.
8
CHAPTER 2
‘THE QUINTESSENTIAL CHINESE DREAM’?
HOMEOWNERSHIP AND THE
SUBJECTIVE WELLBEING OF CHINA’S NEXT GENERATION
This chapter presents co-authored work with Russell Smyth. The chapter uses data
from China Family Panel Studies (CFPS), funded by 985 Program of Peking
University and carried out by the Institute of Social Science Survey of Peking
University. The authors would like to thank Choon Wang, Lata Gangadharan, Haining
Wang, Vinod Mishra, Zhiming Cheng and two anonymous referees of China
Economic Review for insightful comments on an earlier version that greatly improved
the paper.
9
Abstract
China has pursued housing policy reform that has successfully transformed a centrally
planned public housing system into a market-oriented one, focused on promoting
private ownership. As a consequence, China has become a nation of homeowners, with
many Chinese aspiring to own their own home. Has this development made the lives
of people better? We examine how homeownership influences the subjective
wellbeing of children, who will be China’s next generation. Utilising national
representative panel data from China Family Panel Studies, we find that children aged
10-15 years of homeowners have 2.79 percentage points higher subjective wellbeing
than children of non-homeowners. This finding continues to hold after we use
alternative approaches to address the endogeneity of homeownership status and
implement a number of other robustness checks. Our results also suggest that parental
inputs into their children’s education, investment in home maintenance, the quality of
the neighbourhood and parents’ emotional support for their children are channels
through which homeownership influences children’s subjective wellbeing.
Keywords: subjective wellbeing; happiness; homeownership; children; China
10
2.1
Introduction
Owning one’s own home is an important objective for many people and
homeownership potentially has important economic and social implications for both
the homeowner and their children. Yet, while the effects of homeownership on various
aspects of children’s objective wellbeing are well documented,3 the effect of
homeownership on children’s subjective wellbeing (SWB)4 has received very little
attention in the literature. Some studies have considered the SWB of children (see e.g.
Casas & Rees, 2015; Migliorini, Tassara & Rania, 2018; Rees & Bradshaw, 2018;
Tomyn & Cummins, 2011; Tomyn, Fuller-Tyszkiewicz, Cummins & Norrish, 2017).
There is only one study that considers the relationship between homeownership and
SWB of children. In a cross-sectional study of the determinants of SWB of 11 years
old children in the UK, Rees and Bradshaw (2018) find that children living in rental
houses had lower SWB than those living in houses owned by their parents.
We test whether homeownership status has a causal effect on the SWB of children in
China and examine the channels or mediators via which it may affect the child’s SWB.
To do so, we use nationally representative longitudinal data from China Family Panel
Studies (CFPS). Compared with other national datasets that contain information on
children, such as the China Health and Nutrition Survey (CHNS), CFPS has the
advantage that it contains data on both the SWB of children and whether their parents
own their home, along with a rich set of controls that are potentially correlated with
the child’s SWB.
There is by now a considerable amount of literature on the determinants of SWB in
China (see e.g. Asadullah, Xiao & Yeoh, 2018; Cai & Wang, 2018; Chen & Davey,
2008; Cheng et al., 2017; Hu & Coulter, 2017; Li & Liu, 2018; Mishra, Nielsen, Smyth
& Newman, 2014; Smyth, Nielsen & Zhai, 2010) of which, a subset has examined the
effect of homeownership (see e.g. Cheng, King, Smyth & Wang, 2016; Hu, 2013) on
the SWB of the adult population. There is also a growing literature on the determinants
of different aspects of SWB of children in China. For example, Wu (2014) studies the
effect of China’s one-child policy and finds that being an only child significantly
3
For a review on some of the recent literature, see Zavisca and Theodore (2016).
The term ‘subjective wellbeing’ is used interchangeably in the literature with ‘life satisfaction’ and
‘happiness’. We use the term ‘subjective wellbeing’ throughout this paper.
4
11
lowers the SWB of children. Other studies include Chen and Liu (2012) and Lau and
Li (2011), who find that perceived parental warmth, the level of engagement of one’s
family and level of social capital at school are determinants of various aspects of SWB
of children in China. There are, however, no studies that examine the relationship
between homeownership and SWB of children in China.
Our contribution is related to two strands of literature. One strand of literature are
studies focused on the relationship between homeownership and objective outcomes.
Studies have shown that children of homeowners receive better grades (see e.g. Barker
& Miller, 2009; Haurin, Parcel & Haurin, 2002; Whelan, 2017); have higher rates of
high school graduation (see e.g. Aaronson, 2000; Green & White, 1997); are better
behaved (see e.g. Boyle, 2002; Grinstein et al., 2012; Haurin et al., 2002); have better
health (Clair, 2019); experience lower rates of teen pregnancy (see e.g. Blau, Haskell
& Haurin, 2019; Green & White, 1997), have lower rates of criminal conviction (Blau
et al., 2019), are less likely to end up on welfare (Blau et al., 2019) and have better
lifetime prospects in general (see e.g. Dockery et al., 2014) than children of renters.
A related literature to which we contribute are studies on housing status more
generally, including housing insecurity, housing quality, overcrowding and residential
mobility, and subjective child outcomes, such as cognitive development, emotional
and social well-being and mental health. One set of studies finds that children living
in homes owned by their parents have fewer emotional and behavioral difficulties
(Rees, 2018). A second set of studies finds an association between housing insecurity,
including housing affordability, and cognitive impairment in children (see review in
Leventhal & Newman, 2010). A third set of studies has found a negative association
between excessive moving and children’s cognitive and emotional outcomes (see e.g.
Gambaro & Joshi, 2016; Jellyman & Spencer, 2008). A fourth set of studies find that
children who live in poorer quality housing experience lower emotional wellbeing and
poorer mental health (see review in Clair, 2019). Other studies have found that
overcrowding contributes to children’s emotional problems (Park, Fertig & Allison,
2011).
Our novel contribution is that we present the first study to examine in depth the
relationship between homeownership and the SWB of children. We differ from Rees
12
and Bradshaw (2018) in important respects. The first is in terms of focus. While our
focus is on homeownership and SWB of children, homeownership was just one of
many variables that Rees and Bradshaw (2018) considered in a more general study of
the SWB of children. The second is that while Rees and Bradshaw (2018) used crosssectional data and do not address endogeneity, we use panel data and employ a range
of approaches to address endogeneity.
In presenting the first comprehensive study of the relationship between
homeownership and SWB of children, we contribute to the existing literature on
housing status and child outcomes in several important ways. First, existing research
on homeownership and child wellbeing has focused on factors likely to affect
children’s future wellbeing or becoming. However, Clair (2019) suggests that just
focusing on future wellbeing gives only a partial picture of the child’s overall
wellbeing. To get a holistic overview of the effects of homeownership on the child’s
wellbeing, it is essential to also consider the effect on their present wellbeing, reflected
in their SWB. Second, there is increasing interest in what determines children’s SWB,
including housing status, that has not been explored in the literature (Clair, 2019). This
interest reflects greater attention among economists to indicators of social progress
other than GDP more generally (see e.g. Organisation for Economic Co-operation and
Development [OECD], 2009; 2015; Stiglitz et al., 2009). Third, while studies have
considered the relationship between housing status and emotional outcomes more
generally, these studies have focused on emotional problems in children. The positive
psychology movement (Seligman & Csikszentmihalyi, 2000) has shifted the focus
from factors associated with problematic outcomes to consider those factors that
improve our wellbeing or make us happier. The existing literature on housing status
and child outcomes does not address the role that housing status can play in
contributing positively to children’s happiness.
Our preferred results suggest that children of homeowners have 2.79 percentage points
higher SWB than children of non-homeowners. Moreover, we find heterogeneity in
the SWB of children across genders, residential location and migration status of the
household. Our results remain robust to a range of checks, including alternative ways
to address potential endogeneity of homeownership, parental income and the SWB of
the child’s father.
13
This result contributes to the literature on the welfare implications of long-term social
policy – in this case housing policy – change. Over the last decade, the Chinese
government has expanded its affordable housing programs - such as the Economical
and Comfortable Housing Program and the Housing Provident Fund Program – as
vehicles to promote homeownership (see e.g. Chen & Deng, 2014; Deng, Shen &
Wang, 2011). Our results suggest that programs, such as this, designed to increase
housing affordability, can increase the welfare of Chinese children. In an era in which
Chinese parents are going to increasing lengths to ensure the happiness, and secure the
future of the “little emperor” generation (Mo & Burton-Bradley, 2018), our results also
have important practical implications for parents. They suggest a further avenue
through which parents can contribute to their child’s happiness.
2.2
Conceptual framework and channels
The conceptual framework we employ is a variation of the home production model
(Ben-Porath, 1967). This framework has been used to model child objective outcomes
in terms of a good produced in the home, which is treated as a function of the child’s
characteristics, the parents’ characteristics, parental inputs, homeownership status and
other features of the child’s environment, including housing, neighbourhood and
schooling characteristics (see e.g. Bernal & Keane, 2011; Blau, 1999; Blau et al., 2019;
Cunha & Heckman, 2008). While this framework is typically used to model the child’s
objective outcomes, if one sees these in terms of the child’s future wellbeing or
becoming, as it is described in the psychology literature, it is a natural extension to
model the child’s present wellbeing, captured by SWB, in the same way. Adopting
such an approach where we model subjective responses on SWB is also consistent
with studies, such as Cunha and Heckman (2008), that model the child’s subjective
responses about noncognitive attributes within a home production framework.
Our primary interest is in the role that homeownership status plays in influencing the
child’s SWB, controlling for the child’s and parents’ characteristics, parental inputs
and environmental characteristics. The existing literature has identified five main
channels through which homeownership may influence the child’s objective outcomes
(future wellbeing) that are also likely to be true for the child’s SWB. We outline each
of these in turn. Later in the paper, we test whether these channels act as mediators.
14
Parental inputs into monitoring and nurturing their children
Green and White (1997) posited that parents acquire new management skills
associated with property ownership, such as budgeting, planning and problem solving,
that transfer to successful parenting practices via learning by doing. As such, parents
who are homeowners can be expected to take better care of their children. Children
who are better cared for will be happier. It is likely that in transferring these skills to
their children, parents who are homeowners will be more engaged with their children
and this is expected to reinforce the positive effect on their child’s SWB, independent
of the acquisition of new skill sets.
More parental involvement in the neighbourhood, including nurturing others’
children
Green and White (1997) noted that another difference between homeowners and
renters is that the former has a larger financial stake in their neighbourhood because
most of their wealth is tied up in their residence. Moreover, homeowners face a higher
moving cost so they tend to remain in the same location longer than renters. Hence,
homeowners have a greater incentive than renters to improve the neighbourhood
environment which may contribute not only to the happiness of their own children, but
the children of others, who will often also be the children of other homeowners, given
that homeownership tends to be concentrated.
Home owners invest more in home maintenance and repairs
Rational choice theory suggests that homeowners have greater incentive to protect
their investment in their properties than renters. As such, homeowners will invest more
in home maintenance and repairs in order to realize the capital gains of their
investment. Hence, owner-occupied housing has fewer health hazards, fewer structural
impediments and is likely to be better-quality housing than renter-occupied housing
(Haurin et al., 2002). This creates a cleaner and safer home environment for children,
which is likely to contribute to higher SWB.
Home owners live in better neighbourhoods
Communities occupied mostly by homeowners tend to have more stable
neighbourhoods, better schools and better public facilities (Mohanty and Raut, 2009).
Living in better neighbourhoods has been shown to have a positive causal effect on a
15
range of objective outcomes for children, such as better performance at school and
income later in life (see e.g. Chetty, Hendren & Katz, 2016). We expect children living
in better neighbourhoods to be happier because they provide safer environments in
which to live and play and better access to community facilities. Homeownership may
also promote higher levels of parental engagement with their children as owners live
in communities with greater opportunities for school participation and involvement in
neighbourhood activities with their children (Grinstein-Weiss et al., 2012).
Parents’ self- esteem and emotional support for their children
Owning one’s own home increases satisfaction and self-esteem and this may translate
into a more supportive psychological home environment for their children, potentially
contributing to higher SWB (Blau et al., 2019). The opposite side of the coin, however,
is that homeowners who have large mortgages can experience financial stress when
paying off their home loan, which can translate into increased emotional stress (Cheng
et al., 2016). This may manifest in conflict at home over money and/or one or more
parents working longer hours to make ends meet with adverse effects on emotional
support for, and the SWB of, their children.
Overall, these competing channels suggest competing hypotheses about the effect of
homeownership on the SWB of children. The first four channels suggest that the
relationship should be positive. The fifth channel suggests that the relationship may be
negative, at least in certain circumstances, when parents have large mortgages that
they are struggling to service. Homeownership may also restrict residential mobility
and make it more difficult for parents to be flexible enough to take advantage of
economic opportunities in other localities. This could also have an adverse effect on
the SWB of children, particularly if the property is located in a depressed area or in a
neighbourhood with poor facilities.
2.3
China’s context
China represents an interesting case in which to situate a study of the relationship
between homeownership and SWB of children. For decades, homeownership was
regarded as the quintessential American dream (Goodman & Mayer, 2018).
Homeownership is now the quintessential Chinese dream. As Sito and Liu (2018) put
it: “What was once a very American dream is now stitched into the hearts of the
16
ordinary Chinese. Homeownership has become the ultimate symbol of success in
China, the mark of adulthood, readiness for a family, and ownership of one’s financial
destiny”. China is becoming a nation of homeowners, with one of the world’s highest
rates of homeownership. Around 90% of households in China own their own home.
The homeownership rate for millennials - i.e. those born between 1981 and 1998 - is
70%, which is much higher than the average global homeownership rate of 40%
(Hongkong and Shanghai Banking Corporation [HSBC], 2017). The homeownership
figure for millennials is expected to rise further with one report suggesting that 91%
of millennial non-homeowners are intending to purchase a house in the next five years
(HSBC, 2017).
The Chinese case is instructive for several reasons. First, pretty much all of the existing
literature on homeownership and child outcomes focus on the United States or Western
Europe. There is need for broader evidence, particularly from developing country
settings. As Ferguson, Cassells, MacAllister and Evans (2013, p. 438) put it, the lack
of evidence on homeownership and child outcomes outside of North America and
Western Europe is “an important gap in the literature”. In contributing to the literature
on the relationship between homeownership status and child outcomes in general, we
help to address this gap.
Second, the housing crisis in the United States and United Kingdom that followed
foreclosures in the Global Financial Crisis, focused attention on the effects of this
development for children’s lives (see e.g. Clair, 2019; Leventhal & Newman, 2010).
Studying China brings a different dimension to the table. Rather than concentrate on
the effects of a sharp decline in homeownership on children’s wellbeing, it allows us
to examine whether a substantial increase in homeownership rates brings with it added
benefits for children’s wellbeing.
There are good reasons to think that China may differ along some of the conceptual
links discussed in Section 2 to the United States or United Kingdom. Specifically,
China has become a nation of homeowners, almost overnight, so the learning by doing
effect, first articulated by Green and White (1997) from owning a house en masse can
be expected to be particularly pronounced in China, strengthening the role of parental
inputs into monitoring, and nurturing, their own children. The commodification of
17
housing en masse in China has also given rise to new kinds of neighbourhoods and
sense of neighbourhood attachment within a short period, which does not have
parallels in western contexts. The limited empirical evidence on this issue which does
exist suggests that homeownership in China is associated with strong neighbourhood
attachment, which is mainly based on satisfaction with the physical environment and
sense of belonging (Zhu, Breitung & Li, 2012). This suggests that the role played by
investment in homeownership, maintenance and neighbourhood stability may be
particularly strong in the Chinese case, compared to western contexts.
Finally, the high cost of housing in China has contributed to very high levels of
mortgage debt. Personal home mortgages in China expanded eightfold from three
trillion RMB in 2008 to 24.9 trillion RMB in 2018 (Caixin, 2018), making people
“slaves to their house” (fang nu). Financial stress associated with mortgage
repayments is likely to lead to heightened emotional stress, potentially strengthening
the role played by parental self-esteem and emotional support linking homeownership
status with children’s SWB in China.
Taken together, these specific features of the Chinese context suggest that examining
the relationship between homeownership status and children’s SWB in China can
extend our theoretical understanding of the link between homeownership status and
child outcomes outside the North American or Western European context.
Specifically, we would expect the links between homeownership status and children’s
SWB in China to be strong.
2.4
Data
The CFPS survey, administered by the Institute of Social Science Survey at Peking
University, uses a multi-stage probability-proportional-to-size sampling design to
gather individual-, family- and community-level longitudinal data. The survey, among
other issues, focusses on the economic and social activities of the Chinese population
and, as such, contains a wealth of information covering topics such as economic
activities, financial resources, family and community resources, family dynamics,
educational outcomes, behavioural activities, and subjective views on various aspects
of one’s life.
18
The baseline survey in 2010 successfully interviewed 14,960 households, consisting
of 42,590 individuals living in these households in 25 provinces or administrative
equivalents, representing almost 95% of the total population. The follow-up surveys
at an interval of two years - 2012, 2014 and 2016 - re-surveyed the initial households
and their respondents. Given the focus of this study is on the SWB of children, we
focus on children in the 2012 and 2014 surveys aged between 10 and 15 who were
interviewed with similar survey modules. In total 1,813 children (723 respondents in
2012 and 1,090 respondents in 2014) provided valid information for the key variables
in this paper. The choice of 2012 and 2014 waves for the main analysis was based on
the availability of the most complete data for the construction of the multi-item index
that we use to measure children’s SWB. The 2010 and 2016 waves had missing data
for some items, while some other items were not consistently measured in these waves.
Data for all four waves are used in a robustness checks, which uses a modified SWB
index with fewer items, reflecting the lack of consistent data over the four waves. This
check shows our results to be robust to different time periods and measures of SWB.
Since the focus of this study is on the SWB of children, of particular importance is
how we obtain subjective data from children. Amato and Ochiltree (1987) provide
empirical evidence that children aged as young as eight and nine years old have the
ability to provide valid data. We use data from Child Module in the CFPS survey in
which children who are between the age 10-15 years answer questions contained in
that particular module of the survey. Data on children below the age of 10 were not
used because their responses were completed by an adult household member, which
cannot be substituted for children’s self-reported data (White-Koning et al., 2005)
while those above the age of 15 responded to the Adult Module which has a different
set of questions. To account for the difficulty which children might experience in
understanding the vocabulary used in the survey and the concepts about which they
are questioned, we only draw on simple and straightforward questions which are free
of ambiguity. In particular, we use ten subjectively measured response items that were
consistently measured over the 2012 and 2014 waves to create the SWB index for our
study. These questions, measuring different aspects of SWB, are (1) How would you
rate your academic performance? (2) Do you think that you are a good student? (3)
Are you satisfied with your school? (4) Are you confident about your future? (5) Do
you think you are popular? (6) Is it easy for you to get along with others? (7) Are you
19
satisfied with your class advisor? (8) Are you satisfied with your foreign language
teacher? (9) Are you satisfied with your Chinese language teacher? (10) Are you
satisfied with your math teacher?
The specific choice of the questions in the index is partly dictated by data availability,
but we wanted to ensure that there is a focus on wellbeing at school. Several studies
(e.g. OECD, 2015) suggest school forms a central part of children’s lives so we believe
that this is appropriate especially when we are involving children between the ages 1015. The advantage of using the ten items is that we can construct a multi-item index of
SWB, which, it has been argued, is more reliable (see e.g., Angner, 2010; Morris,
2017; Smyth et al., 2010) than the single item index typically employed by economists.
Since the questions in CFPS are measured on different Likert scales, we use the
‘percentage of scale maximum’ method to convert raw scores into standardised scores
from 0-100 as discussed in Cummins and Lau (2005). In order to combine these ten
responses into one index, these variables were subjected to factor analysis using
principal component analysis in each wave. The results of the factor analysis are
presented in the appendix in Table A2.1. The factor analysis shows that factor loadings
of all these ten items are above 0.42 with the diagnostic tests of Bartlett test for
sphericity showing that the variables are not inter-correlated. The Kaiser-Meyer-Olkin
(kmo) score is around 0.79 indicating that the sample is acceptable, and the Cronbach
alpha value is moderately high at 0.77. Each child’s ten response items were then
averaged with 0 indicating the lowest, and 100 the highest, SWB with the average
score used to denote the child’s SWB.
The main independent variable of interest in this study is the homeownership status of
the household. CFPS classifies homeownership types in at least seven different
categories. These are: (1) property rights solely owned by a family member [full
homeownership] (2) property rights partly owned by a family member [partial
homeownership]; (3) public housing (gong fang) provided by the work unit (danwei)
[minor homeownership]; (4) cheap public rental housing; (5) public rental housing;
(6) commercial housing rented in the market; and (7) living with friends or relatives.
In our analysis we use a dichotomous variable denoted as “1” for homeowners who
20
have full homeownership while the rest are summed together as “0” representing nonhomeowners.5 Data on this variable in the CFPS sample is given in Figure 2.1.
CFPS also includes information on whether those who own their own home have a
mortgage and the amount of repayments on the mortgage. We examine whether their
parents owning a home with a mortgage affects the SWB of the children living in the
home. Just under 90% of parents in the sample had full homeownership of their homes,
while about 8% of parents in the sample had received a loan to purchase or construct
their homes. These figures are representative of China as a whole (Trading Economics,
2018).
Figure 2.1
Diagrammatic representation of home tenure status in the total
sample
10.92%
7.83%
Homeownership: Purchased
without financing - 81.25%
Homeownership: Received
loan for housing - 7.83%
No Homeownership - 10.92%
81.25%
Source: China Family Panel Studies
5
In China, homeowners can have full, partial or minor ownership (Cheng et al., 2016). Partial ownership
is where the owner does not have a state-issued property deed and are usually acquired with housing
purchased at prices subsidised by governments or enterprises. Minor homeownership (gong fang) refers
to housing with limited or no property rights, built by the state or work units and rented/allocated to
households. We also tried disaggregating homeownership into full ownership, partial ownership and
minor ownership. When we did this, the results for partial and minor ownership were insignificant, most
likely reflecting the very small percentage of respondents with partial (2.87%) and minor ownership
(0.83%) in the sample.
21
Figure 2.2 shows that the average SWB of children in the sample is 73.07 percentage
points. The International Wellbeing Group (2013) reports that the normative range for
adult populations is 70-80 percentage points. This appears true for child samples as
well. Migliorini et al. (2018), using the multi-item Personal Wellbeing index (PWI),
which is similar in construction to the SWB index used in this study, finds that SWB
is 71.3 percentage points for eight-year old children in Italy. Xu and Xie (2015) find
that the SWB of children in China is 73.2 percentage points using an index composed
of subjective measures of popularity, happiness, self-confidence and how easy going
the child perceives himself or herself to be.
A simple breakdown of our data suggests that the children of homeowners have an
average SWB index of 73.34, while children of non-homeowners have an SWB index
of 70.84. Further disaggregation of the data shows that for subsamples based on
gender, residential location and migration status of households, the mean SWB for
children of homeowners is higher than non-homeowners.
Figure 2.2
Subjective wellbeing by categories of homeownership
76
74.71
75
74
73.8
73.07 73.34
73
72.79
72.13
71.57
72
71
71.6
71.09
70.84
70.3
70.11
69.74
70
69
68
Full sample
Boys
Girls
Urban
22
Rural
Migrants
Non-Homeowners
Homeowners
Non-Homeowners
Homeowners
Non-Homeowners
Homeowners
Non-Homeowners
Homeowners
Non-Homeowners
Homeowners
Non-Homeowners
Homeowners
: those Non-Homeowners
: those Homeowners
67
Full sample
SWB scorers
73.53
73
Locals
We use a rich set of controls. These include variables with respect to children’s
personal attributes (age, gender, education expectations); household characteristics
(family income, household size, migration status, residential area, child’s family
capital (level of trust that the child has in his/her parents); parental characteristics (if
parents are supportive of the child, the SWB of the parents, which is measured by the
‘happiness score’ of the father and marital status of the parents); housing
characteristics (type of house, housing tenure); neighbourhood social capital (level of
trust that the child has in his/her neighbours) and community social capital (level of
trust that the child has in community government officials).
Table 2.1
Descriptive Statistics
Variables
Age (years)
Boys (%)
Child education expectation (years)
Ln family income
Household size
Urban (%)
Migrants (%)
Family social capital (lowest = 0, highest = 100)
Parent encourage child (punish = 0, encourage = 1)
Happiness score of father (lowest = 0, highest = 100)
Parent married (%)
Type of house:
Apartment (%)
Bungalow (%)
Quadrangle courtyard (%)
Villa (%)
Condominium villa (%)
Low-rise house (%)
Housing tenure (<15 years=0, 15 years=1) (%)
Neighbourhood social capital (lowest = 0, highest =
Community social capital (lowest = 0, highest = 100)
Province (25 provinces)
Mean/Proportions
12.43
53.67
15.37
10.35
4.77
45.62
23.61
94.14
88.03
59.60
97.30
18.86
47.21
5.79
0.99
0.22
26.92
28.30
66.81
61.23
See Appendix Table A2.2
Table 2.1 presents descriptive statistics of the variables used in this study. These
variables are described in detail in the appendix Table A2.2. Just over 50% of the
sample were boys, 46% were residing in urban areas, and about 24% were migrants.
The natural log of household income was 10.35, the average family size was five
family members and 97.3% of the children were born to parents who were legally
married.
23
The average years of education expectation for children were 15.37 years, which
approximately equates to finishing junior college. Other family characteristics show
that fathers are moderately happy, children have substantial trust in their parents and
about 88% of parents always encouraged their children to do well at school. There are
28.3% of households who have lived in the same house for more than 15 years with
47.21% living in bungalows, 26.92% living in low-rise houses and 18.86% living in
apartments, while 7% lived in either a quadrangle courtyard, villa or condominium
villa. Children in the sample had moderate levels of trust in their neighbourhood and
community officials.
2.5
The Empirical Model
Since we are particularly interested in the mechanism underpinning the relationship
between homeownership and children’s SWB, we estimate the following empirical
regression model:
𝑆𝑊𝐵𝑖𝑡 = 𝑎0 + 𝛽1 𝐻𝑖𝑡 + 𝛽2 𝑿′𝑖𝑡 + 𝛾𝑝 + 𝜏𝑡 + 𝜀𝑖𝑡
(2.1)
where 𝑆𝑊𝐵𝑖𝑡 is the SWB index for the respondent 𝑖 in time 𝑡; 𝐻𝑖𝑡 captures the
homeownership status of the respondent’s household while the vector 𝑿′𝑖𝑡 captures a
number of personal characteristics (age, gender, education expectation of the child),
household characteristics (family income, household size, either in urban or rural area,
is the family classified as migrant and the level of trust the child has in his/her parents),
parental characteristics (whether parents encourage child in his/her school work,
happiness score of the father, whether parents are married), households housing
characteristics (type of house, duration of stay at the current location, whether received
loan for housing); and neighbourhood and community characteristics (level of trust in
the neighbours and local government officials). We also control for provincial fixed
effects, 𝛾𝑝 to account for permanent differences across provinces and include year
dummies, 𝜏𝑡 to account for time-varying national determinants of homeownership and
wellbeing. 𝑎0 and 𝜀𝑖𝑡 are respectively, the constant and error term in the model.
One could estimate equation 1 using ordinary least squares (OLS) or an ordered choice
model. Ferrer-i-Carbonell and Frijters (2004) show that the results are not sensitive to
24
the choice of OLS, that treats SWB as cardinal, or an ordered logit/probit model, that
treats SWB as ordinal. Ng (1997) suggests treating SWB as cardinal on theoretical
grounds and, hence, favours the use of OLS. Since, we utilise two waves of CFPS, in
our main results we report pooled OLS for the 2012 and 2014 waves for children aged
10-15, with robust standard errors, clustered at the household level.6 Additionally, to
ensure that the treatment of SWB as cardinal or ordinal does not affect our results, we
also re-estimate the model using ordered logit and probit models. We also estimate our
model for various sub-samples of the data as well as evaluate the role of different
forms of homeownership on the SWB of children.
A potential econometric issue faced when attempting to find the causal effect is that
unobservable variables may affect the correlation between homeownership and the
child’s SWB, despite the reasonably long list of control variables. Technically
speaking, a variable is endogenous if it is correlated with the error term of the
regression for any reason. It is possible that parents who own their homes may be
systematically different from parents who rent and the same characteristics that make
the homeowner parents more likely to own may also make them more likely to bring
up happy and successful children (see e.g. Haurin et al., 2002; Lerman & McKernan,
2008). It may also be that we are not accounting for some omitted or unobserved
factors (e.g. attitude, motivation, life goals and financial literacy) that affect the
parents’ decision to own, which are correlated with both the child’s SWB and
homeownership. It may be that people who own their own homes have a higher work
ethic or are more industrious and arguably are more likely to invest more in their
children and, as a result, raise happier children. If so, homeownership may be
endogenous.
Ideally, to attribute a causal interpretation to the effects one would utilize a valid
external instrumental variable (IV) which is correlated with homeownership, but is not
correlated with the child’s SWB except via their parents’ homeownership status. We
explored a number of potential candidates for a valid external instrument, drawing on
6
Of the 1,813 children in the sample, there are 1,462 who are a single child (80.64%), 280 who are
from a two-child family (15.44%), 63 who are from a three-child family (3.47%) and eight who are
from a four-child family (0.44%). Clustering at the individual or community level does not affect our
conclusions.
25
variables at the provincial level;7 however none of these passed the diagnostics for a
valid instrument.
Hence, in order to address the endogeneity of homeownership in the absence of a
suitable external IV, we employ the approach proposed by Lewbel (2012), which
utilizes a heteroskedastic covariance restriction to construct an internal IV. The
Lewbel (2012) method has been shown to work in instances in which there are weak
instruments (see e.g. Kelly, Dave, Sindelar & Gallo, 2014) or no instruments at all (see
e.g. Millimet & Roy, 2016; Mishra & Smyth, 2015). Both Lewbel (2012) and Mishra
and Smyth (2015) show that estimates produced using the Lewbel approach are
consistent with those produced using a conventional external IV in cases in which a
suitable external IV is available.
The Lewbel (2012) method entails estimating the following specifications:
Y1= X Iβ1 + Y2ϒ1+ξ1
ξ1=α1U + V1
(2.2)
Y2= X Iβ2 +ξ2
ξ2=α2U + V2
(2.3)
Assume Y1 is SWB, Y2 is the homeownership status of the parents and that U denotes
unobserved characteristics, such as personal energy, attitude towards work or life
goals. V1 and V2 are idiosyncratic errors. Lewbel (2012) uses heteroskedasticity in the
data to estimate the IV regression. Lewbel (2012) suggests that one can take a vector
Z of observed exogenous variables and use [Z-E(Z)] ξ2 as an instrument if:
E(X ξ1)=0, E(X ξ2), cov(Z, ξ1, ξ2) = 0
(2.4)
and there is some heteroskedasticity in ξj. The intuition behind why Z-E(Z)]ξ2 works
as an instrument is that identification occurs by having regressors that are not
correlated with the product of the heteroskedastic errors. The point is that the vector Z
could either be a subset of X or equal to X. Using the above chosen set of instruments,
7
Potential candidates for a suitable instrument that we considered included provincial level data on the
number of construction units, the amount of highway investment, the amount of railway investment, the
number of residential flats built, local government spending on housing security, savings deposits of
households and the provincial level sex ratio, which might influence savings and, hence, funds available
for housing loans.
26
one can use two-stage least squares (TSLS) to estimate the IV regression, as one would
do with conventional IVs. As ξ2 is a population parameter, and it cannot be directly
observed, we use its sample estimate ê2, obtained from the first stage regression and
consequently use the vector [Z-E(Z)]ê2 as IVs. The Lewbel (2012) approach assumes
that there is heteroskedasticity in ξj. The exact form of heteroskedasticity requirement
as derived in Lewbel (2012) is cov(Z, ξ22)≠0. In practice, as an approximation, Lewbel
(2012) suggests using the estimate of the sample covariance between Z and squared
residuals from the first stage regression on X to test for this requirement, using the
Breusch and Pagan test for heteroskedasticity.
In addition to modelling for the endogeneity of homeownership, we also suspect that
other important variables such as family income and the happiness score of the father
may be endogenous. Studies on the determinants of SWB, such as Cheng et al. (2016)
and Knight, Song and Gunatilaka (2009), argue that unobserved adult personal
characteristics such as personal energy, might increase income and SWB. We
recognise that this potentially can be the case in our study as well. Parental energy is
likely to increase household income and, at the same time, influence how parents take
care of their children and the kind of home environment that they provide for their
children. Unobserved parental characteristics, such as self-esteem and personal
energy, may increase the father’s happiness score which can also affect how he
interacts with, and raises, his offspring. In addition, there may also be reverse causation
running from the SWB of the child to the happiness of the father if, as seems likely,
the happiness of the father depends at least in part on the SWB of his child.
We address these endogeneity concerns using external instruments, in addition to
internally generated instruments using the Lewbel (2012) method. Specifically, we
instrument for family income using the father’s level of education, consistent with
studies such as Knight et al. (2009), who instrument for income using father’s
education level in their study of the determinants of SWB in rural China. We
instrument for the happiness score of the father using his job satisfaction. Several
studies show that one’s job satisfaction and life satisfaction are correlated (see e.g.
Mishra et al., 2014). However, job satisfaction is unlikely to be correlated with the
child’s SWB, except through the happiness score of the father.
27
As an alternative strategy to the Lewbel (2012) method for addressing endogeneity of
homeownership status, following previous studies that have estimated the impact of
homeownership on adult SWB, such as Cheng et al. (2016) and Xu and Xie (2015),
we use the matching estimates of the average treatment effects of homeownership on
the child’s SWB. Specifically, we apply propensity score matching (PSM), proposed
by Rosenbaum and Rubin (1983), on the standard conditional independence
assumption that, conditional on a set of variables, the treatment variable is independent
of potential outcomes. To ensure the robustness of the PSM results, a region of
common support is selected and we applied different matching methods, including
nearest neighbour matching, radius matching, kernel matching and stratification
methods to assess the range of estimates from the different methods.
As a further robustness check, we re-run the main model’s specification over all the
four waves and over different combinations of waves depending on data availability
to ascertain if the effect of homeownership on SWB of children is consistent and not
biased to different waves and measures. Additionally, in order to evaluate if the results
are robust to variations over time, we examined the relationship between
homeownership and SWB of children for a small subset of 216 children who were
interviewed in 2010, 2012 and 2014 using the same child questionnaire, giving
consistent data for these children over these three waves.
In Section 2.2 we identified several channels through which homeownership may
influence the child’s SWB. To examine the role of these channels, we examine the
effect of several mediators on the relationship between homeownership and SWB
using structural equation modelling (SEM), implemented with the sem command in
STATA 15. Following Powdthavee and Wooden (2015), we bootstrap the standard
errors with 200 replications.
2.6
Empirical Results
The main results estimated with pooled OLS with cluster-robust standard errors are
presented in Table 2.2. In all models we control for year and province fixed effects. In
column (1) we examine the relationship between homeownership and SWB without
controls, while in column (2) we control for the child’s attributes. In column (3) we
additionally control for the child’s household characteristics, while in column (4) we
28
Table 2.2
Determinants of subjective wellbeing for children, CFPS (OLS results)
Variables
Homeownership Status:
Full homeownership (ref: no)
Child personal characteristics:
Age
Age2
Gender (ref: Boys)
Child education expectation (in years)
Household characteristics:
Ln family income
Household size
Urban
Migrants
Family social capital
Parental Characteristics:
Parent encourage child
Happiness score of father
Parent married
Household Housing characteristics:
Type of house (Ref: Low-rise house)
Apartment
Bungalow
Condominium villa
Quadrangle courtyard
Villa
Housing tenure: more than 15 years
Received loan for housing
Neighbourhood and Community capital:
Neighbourhood social capital
Community social capital
Province
Year dummy
Constant
N
Adj. R-squared
1
2.4664**
Yes
Yes
63.0802***
1,813
0.0343
2
(2.32)
(22.28)
3
4
5
6
2.7560***
(2.67)
2.7826***
(2.86)
2.8264***
(2.90)
3.0075***
(3.05)
2.7994***
(3.00)
-2.8822
0.0898
-1.9703***
0.8497***
(-0.95)
(0.74)
(-3.41)
(8.60)
-5.7304*
0.2049*
-1.7499***
0.7719***
(-1.96)
(1.75)
(-3.08)
(7.89)
-5.5456*
0.1968*
-1.6825***
0.7588***
(-1.90)
(1.69)
(-2.97)
(7.75)
-5.6413*
0.2010*
-1.6941***
0.7491***
(-1.93)
(1.72)
(-2.98)
(7.60)
-3.7146
0.1272
-1.7798***
0.7245***
(-1.30)
(1.11)
(-3.28)
(7.67)
0.0370
-0.2604
1.1225
-0.8856
0.2367***
(0.13)
(-1.15)
(1.36)
(-0.98)
(9.51)
-0.0001
-0.2806
1.0605
-0.8471
0.2331***
(-0.00)
(-1.23)
(1.28)
(-0.94)
(9.46)
-0.0392
-0.2248
0.3796
-0.2894
0.2323***
(-0.14)
(-0.94)
(0.39)
(-0.30)
(9.39)
-0.0709
-0.1558
0.9310
-0.8520
0.1391***
(-0.25)
(-0.71)
(1.02)
(-0.92)
(5.33)
2.0024**
0.0115
1.1732
(2.17)
(0.99)
(0.63)
2.0101**
0.0120
1.0896
(2.17)
(1.03)
(0.58)
1.8463**
0.0121
1.0845
(2.07)
(1.11)
(0.64)
1.6839*
0.5415
-1.5210
-0.0625
3.0916
-0.3266
0.0394
(1.65)
(0.65)
(-0.27)
(-0.05)
(1.52)
(-0.47)
(0.03)
2.1054**
0.6058
-3.1480
0.0784
1.4494
-0.1991
0.7085
(2.12)
(0.76)
(-0.59)
(0.06)
(0.71)
(-0.30)
(0.61)
0.1137***
0.0746***
Yes
Yes
53.7514***
1,813
0.2101
(7.68)
(6.26)
Yes
Yes
73.9739***
1,813
0.0894
(3.92)
Notes: t-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01.
29
Yes
Yes
72.2808***
1,813
0.1372
(3.91)
Yes
Yes
68.7976*** (3.70)
1,813
0.1391
Yes
Yes
69.4787***
1,813
0.1377
(3.72)
(2.95)
extend the model to also control for parental characteristics. In column (5) we add
housing characteristics. The most complete specification in column (6) contains our
preferred estimates which has full set of controls.
The main finding in column (1) is that the coefficient on the homeownership variable
is positive and significant. This finding is robust to controlling for other characteristics
across various specifications from columns (2) to columns (6). The final specification
in column (6) shows that the SWB of children of homeowners is 2.79 percentage points
higher than children of non-homeowners. The effect of homeownership on SWB of
children is equivalent to about one and half times the effect of having supportive
parents. The result is consistent with our hypothesised positive links between
homeownership and SWB of children.
The results also show that children whose parents own apartments have 2.10
percentage points higher SWB than those living in low-rise houses. This is largely
because low-rise houses are situated in old traditional neighbourhoods which are
poorly maintained and are in bad condition. However, whether the parents have a
mortgage on the property does not significantly affect the SWB of children. The
relationship between having a home loan and the child’s SWB is consistent with Cheng
et al. (2016) who found that having a home loan has no significant effects on the SWB
of adults in China.
Table 2.3 examines whether the effect of homeownership varies for different
subgroups. In particular, we estimate the heterogeneous effects of homeownership on
children based on their gender, residential location and migration status of households.
The effect of homeownership on the SWB of children is different across genders. The
estimates show that homeownership has a positive and significant effect on the SWB
of boys, while it is positive, but insignificant, for girls. A possible explanation is that
homeownership provides an opportunity for wealth accumulation, financial stability
and residential stability in the future which is arguably more relevant for males than
females (Grinstein et al., 2012). This is particularly applicable in the Chinese context
in which parents often financially assist sons to buy their own first homes, which is
important for success in the marriage market (Hu, 2013).
30
Table 2.3
Determinants of subjective wellbeing in sub-samples, CFPS (OLS results)
Variables
Homeownership Status:
Full homeownership (ref: no)
Child personal characteristics:
Age
Age2
Gender (ref: Boys)
Child education expectation (in years)
Household characteristics:
Ln family income
Household size
Urban
Migrants
Family social capital
Parental Characteristics:
Parent encourage child
Happiness score of father
Parent married
Household Housing characteristics:
Type of house (Ref: Low-rise house)
Apartment
Bungalow
Condominium villa
Quadrangle courtyard
Villa
Housing tenure: more than 15 years
Received loan for housing
Neighbourhood and Community capital:
Neighbourhood social capital
Community social capital
Province
Year dummy
Constant
N
Adj. R-squared
Boys
Girls
Urban
Sub-samples for:
Rural
Locals
Migrants
3.4329***
(2.72)
1.7779
(1.24)
2.7147**
(2.48)
2.4372
(1.38)
2.9025**
(2.49)
2.3363
(1.44)
-5.4426
0.2016
(-1.37)
(1.27)
-2.8889
0.0889
(-0.69)
(0.53)
0.9081***
(7.19)
0.5207***
(3.65)
-0.0789
-0.0164
-0.6096
0.6817***
(-0.02)
(-0.10)
(-0.73)
(4.64)
-5.6482
0.2040
-2.7531***
0.7998***
(-1.40)
(1.26)
(-3.74)
(6.49)
-2.0007
0.0587
-2.1538***
0.7024***
(-0.59)
(0.44)
(-3.50)
(6.73)
-8.2816
0.3138
-0.7317
0.8068***
(-1.48)
(1.40)
(-0.62)
(3.76)
-0.3331
0.0094
2.8796**
-1.6851
0.1251***
(-0.86)
(0.03)
(2.10)
(-1.25)
(3.72)
0.2240
-0.2375
-0.9988
-0.2135
0.1747***
(0.56)
(-0.92)
(-0.86)
(-0.17)
(4.06)
0.7016
-0.1316
(1.52)
(-0.44)
-0.4800
-0.1600
(-1.33)
(-0.54)
-0.4259
-0.0722
0.8584
(-1.31)
(-0.30)
(0.83)
0.8283
-0.3118
(1.38)
(-0.69)
-0.5984
0.1335***
(-0.61)
(3.72)
0.1380***
(3.49)
0.1489***
(4.60)
0.1110**
(2.46)
1.8562
0.0231
2.9824
(1.51)
(1.48)
(1.19)
1.9356
0.0076
-0.6172
(1.49)
(0.51)
(-0.27)
1.6428
-0.0006
-2.0077
(1.23)
(-0.04)
(-0.83)
2.1101*
0.0265*
3.0807
(1.80)
(1.80)
(1.26)
2.0886**
0.0097
2.8207
(1.99)
(0.76)
(1.44)
0.6858
0.0244
-4.3093
(0.40)
(1.11)
(-1.26)
1.2320
0.7922
-1.7036
0.4119
-0.5887
-0.9437
-0.4008
(0.91)
(0.73)
(-0.34)
(0.21)
(-0.20)
(-0.97)
(-0.24)
2.8840**
0.3845
-5.7793
-0.1634
1.0155
0.7914
1.7287
(2.09)
(0.34)
(-0.82)
(-0.09)
(0.33)
(0.90)
(1.17)
1.6531
1.1551
5.4899***
3.2510*
1.2714
0.0712
1.0876
(1.41)
(0.95)
(2.75)
(1.72)
(0.44)
(0.07)
(0.78)
2.9633
0.1098
-12.9783***
-1.5613
4.5312**
-0.3999
0.1537
(1.27)
(0.10)
(-8.28)
(-0.86)
(2.37)
(-0.45)
(0.08)
2.8434**
0.2938
-2.5022
-0.8520
1.3163
-0.2215
0.4449
(2.38)
(0.31)
(-0.42)
(-0.54)
(0.61)
(-0.29)
(0.34)
-0.5681
1.1043
(-0.31)
(0.71)
2.8012
3.4677
-0.9707
1.4571
(1.15)
(0.53)
(-0.66)
(0.57)
0.1137***
0.0800***
Yes
Yes
57.5774**
973
0.2102
(5.80)
(4.89)
0.1167***
0.0707***
Yes
Yes
50.9749*
840
0.1854
(5.12)
(3.92)
0.1175***
0.0634***
Yes
Yes
25.7491
827
0.2193
(5.47)
(3.75)
0.1136*** (5.46)
0.0862*** (5.15)
Yes
Yes
69.0698*** (2.67)
986
0.2096
0.1138***
0.0790***
Yes
Yes
45.2268**
1,385
0.2047
(6.45)
(5.72)
0.1109***
0.0668***
Yes
Yes
77.1747**
428
0.2132
(3.86)
(2.71)
(2.29)
(1.91)
Notes: t-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01.
31
(0.98)
(2.09)
(2.15)
Our results show that the effect of homeownership is more prominent in urban areas
than in rural areas. The estimates show that homeownership significantly improves the
SWB of children in urban areas by 2.71 percentage points, but is insignificant in rural
areas. The significant, and positive, effect of homeownership in urban China can be
attributed to the nature of homeownership in the two locations. Sole homeownership
in urban areas provides urban households more autonomy over housing decisions,
compared to collective nature of house sites in the rural areas. This allows urban
children to better realise the perceived benefits of homeownership, which might not
be the case in rural areas.
Similarly, for children of locals there is a significant and positive effect of
homeownership on their SWB, while homeownership has an insignificant effect on
the SWB of children of migrants. This is consistent with the findings of Cheng, Smyth
and Wang (2013) for the effect of homeownership on the SWB of local adults in China
born after 1980. A possible explanation is that migrants find it difficult to secure homes
in good neighbourhoods, largely because of household registration (hukou) restrictions
and, thus, end up securing homes in lower tier cities and sub-standard crowded
apartments. The associated problems with this housing mean that homeownership for
migrant children is not reflected in higher SWB. However, migrant children’s higher
education expectations and level of trust in their parents, neighbours and community
continue to have a significant positive effect on their SWB.
In Table 2.4, we report results for the mediation analysis using alternative mediators
through which homeownership may influence the child’s SWB. Given the questions
asked in CFPS, we were able to identify proxies for four of the five proposed channels
in Section 2.2. The potential channel for which we could not identify proxies was
parental involvement in the neighbourhood, including monitoring others’ children.
We identify three variables as proxies for parental inputs into monitoring and nurturing
their own children. These are (1) the interviewer’s assessment of the level of care that
parents have in their child’s education, based on the amount of the child’s artwork,
books and study materials in the house; (2) how often parents discuss what happens at
school with their child; and (3) how often parents attend parent-teacher meetings. We
include each of these variables as mediators separately in columns 1-3 of Table 2.4,
together with the same controls as in our main model. Each of these variables are
32
Table 2.4
Structural equation model of the relationship between homeownership and subjective wellbeing
Variables
Full homeownership (ref: no)
Parental inputs into monitoring and nurturing
their children
Home environment
1
2.9904***
(0.9923)
2
2.9381***
(0.9140)
3
2.8811***
(1.1084)
4
3.4034***
(1.0617)
5
3.4034***
(1.0551)
6
5.4253**
(2.4808)
7
3.3179***
(1.1050)
1.6870***
(0.3872)
0.6587**
(0.2608)
Monitoring children
0.9017***
(0.2318)
Nurturing their children
Homeowners live in better neighbourhoods
Cleanliness of neighbourhood
0.3986*
(0.2228)
0.4121*
(0.2232)
Economic condition of the community
Homeowners invest more in home maintenance
and repairs
Home maintenance and repairs
0.8439**
(0.3882)
Parents’ self-esteem and emotional support for
their children
Parents home relationship
-0.3606***
(0.1255)
Emotional support for children
Control variables
Observations
8
2.9611***
(0.8987)
Included
1,760
Included
1,813
Included
1,545
Included
1,702
Included
1,702
Included
248
Included
1,752
0.2630***
(0.0559)
Included
1,800
Notes: (1). Reported results are total (direct and indirect) effects from a SEM. Bootstrapped standard errors (200 repetitions) are in parentheses; * p < 0.10, ** p < 0.05, *** p < 0.01. Standard errors are
bootstrapped with 200 replications. (2). Home environment is the interviewer’s assessment on a scale of 1-5 ‘If parents care about their child’s education in terms of observing items such as child’s artwork,
books, or other study materials in the house’. (3). Monitoring children is the parent’s response to the question ‘How often have you discussed what happens at school with your child since this semester
started/last semester?’ on a scale of 1-5. (4). Nurturing their children is the parent’s response to the item ‘The parents attended parent-teacher meetings at school” on a scale of 1-5. (5). Cleanliness of
neighbourhood is the interviewer’s assessment on a scale of 1-7 of the ‘Cleanliness of the roads in the village/residential community’. (6). Economic condition of community is the interviewer’s assessment
on a scale of 1-7 of the ‘Economic condition of the village/residential community’. (7). Home maintenance and repairs is the parent’s response to the question ‘What was the total expenditure on home repairs
and decoration in the past 12 months?’ This data was only available for 2014. (8). Parents home relationship is the child’s response to the question ‘In the past month, how many times did your parents quarrel
with each other?’ (9). Emotional support for children is the child’s response on the question ‘In the past month, how many times did you and your parents have a heart-to-heart talk?’
33
channels through which homeownership is related to the child’s SWB and the total
effect of homeownership is still positively and significantly related to the child’s SWB.
In columns 4 and 5 of Table 2.4, we report the results for two proxies to test whether
the quality of the neighborhood mediates the effects of homeownership on child’s
SWB. The two proxies are the interviewer’s assessment of the cleanliness of the roads
in the village or residential community and the interviewer’s assessment of the
economic condition of the village or the residential community. In column 6 we test
whether investment in homeownership and maintenance mediates the effects of
homeownership on child’s SWB, where investment in homeownership and
maintenance is proxied by the household’s total expenditure on home repairs and
decoration in the past year. The results in columns 4-6 suggest that each of these
variables are mediators and that the total effect of homeownership continues to be
positively and significantly related to the child’s SWB.
In columns 7 and 8 of Table 2.4 we examine whether parents’ self-esteem and
emotional support for their children mediates the relationship between homeownership
and the child’s SWB. To proxy this construct, we use the child’s response as to the
number of times that his or her parents quarreled with each other and (2) the number
of times that the child and the parent had had a heart-to-heart talk in the past month.
The results in column 7 show that an increase in the number of times that parents
quarreled with each other had a significant negative effect on the SWB of their child.
However, the greater the number of times that the parent and child honestly talked
with each other about their feelings significantly enhanced the child’s SWB.
Overall, the total effect of homeownership on SWB of the child remains positive and
significant in each specification in Table 2.4, even after the inclusion of mediating
variables to capture various channels through which homeownership affects the child’s
SWB.
In Section 2.3 we hypothesized that, given the specific characteristics of home
ownership in China, each of these channels should be more pronounced in China than
in western countries. How do the findings for the pathways compare with extant
studies for the West? An important point to note is that not all studies formally test the
34
potential channels. Many of the best-known studies (eg. Green & White, 1997; Blau
et al., 2019) propose that such channels exist linking homeownership with child
outcomes, but do not formally test the strength of alternative pathways. But, among
extant studies which do, findings have been mixed. For example, Haurin et al. (2002)
found that parental attitudes and the home environment mediates the relationship
between homeownership-child outcome relationship in the United States. Holupka
and Newman (2012), however, found that the homeownership-child outcome
relationship in the United States was not mediated by parental and neighborhood
pathways. Hence, overall, the channels do appear to be stronger in China than in the
West.
2.7
Extensions and robustness checks
In the main results we treated SWB as cardinal. The ordered logit and probit results
are presented in appendix Table A2.3. The effect of homeownership on the SWB of
children is also positive and significant when SWB is treated as ordinal instead of
cardinal.
To this point, we have employed pooled OLS, but are yet to account for the
endogeneity issues raised in Section 2.5. We deal with the issue of endogeneity in
Table 2.5. Column (1) in Table 2.5 reports results obtained using Lewbel (2012) to
instrument for homeownership using the internally generated IV. The Breusch-Pagan
test rejects the null hypothesis of constant variances, which is a precondition to
implement the Lewbel (2012) approach. The OLS estimates are slightly downward
biased as the point estimate after accounting for endogeneity show that the SWB of
children of homeowners is 2.91 percentage points higher than children of nonhomeowners. This is 0.12 percentage points higher than OLS estimates.
Columns (2.1) to (2.3) in Table 2.5 report results in which we use alternative strategies
to deal with endogeneity of income. In column (2.1), we instrument for income using
the education level of the father. The null hypothesis that income is exogenous is
rejected by the Durbin-Wu-Hausman chi-square endogeneity test. The underidentification test rejects the null hypothesis that father’s education level is not
correlated with income. The result of a weak identification test also fails to reject the
null hypothesis that father’s education level is strongly correlated with income. The F35
Table 2.5 Robustness checks (instrumenting endogenous variables)
Homeownership
(1)
TSLS regression
with Lewbel (2012)
IV
Family income
(2.1)
(2.2)
Happiness score of father
(2.3)
TSLS regression
with father’s year
of education and
internal
instruments as IV
TSLS regression with
father’s year of
education as IV
(3.1)
TSLS regression
with Job
satisfaction score
as IV
(3.2)
(3.3)
TSLS regression with
job satisfaction score
and internal
instruments as IV
TSLS regression with
TSLS regression with
Lewbel (2012) IV
Lewbel (2012) IV
Variables
Homeownership Status:
Full homeownership (ref: no)
2.9169***
(2.75) 2.7406***
(2.92)
2.7707***
(3.01)
2.7635***
(3.00) 2.3445**
(2.00)
2.7993**
(3.04)
2.3319**
Child personal characteristics:
Age
-3.7145
(-1.32) -3.5757
(-1.24)
-3.6187
(-1.28)
-3.6479
(-1.29) -1.2779
(-0.31)
-3.9468
(1.40)
-1.3701
Age2
0.1273
(1.13)
0.1224
(1.07)
0.1238
(1.10)
0.1250
(1.11) 0.0232
(0.14)
0.1365
(1.21)
0.0270
Gender (ref: Boys)
-1.7784***
(-3.32) -1.7604***
(-3.26)
-1.7737***
(-3.31)
-1.7658*** (-3.29) -1.9507***
(-2.84)
-1.8085***
(-3.37)
-1.9585***
Child education expectation (in years)
0.7249***
(7.79)
0.7272***
(7.75)
0.7262***
(7.76)
0.7259***
(7.76) 0.7474***
(6.07)
0.7266***
(7.78)
0.7492***
Household characteristics:
Ln family income
-0.0699
(-0.25) -0.5578
(-0.34)
-0.3402
(-0.64)
-0.3475
(-0.67) 0.1585
(0.37)
-0.452
(-0.16)
-0.1804
Household size
-0.1573
(-0.73) -0.0855
(-0.27)
-0.1187
(-0.54)
-0.1147
(-0.52) -0.3471
(-1.40)
-0.1617
(-0.75)
-0.3470
Urban
0.9358
(1.04)
1.0817
(1.06)
1.0118
(1.13)
1.0183
(1.14) 0.8386
(0.74)
0.8823
(0.98)
0.7938
Migrants
-0.8460
(-0.93) -1.0536
(-0.92)
-0.9657
(-1.06)
-0.9651
(-1.05) -1.0240
(-0.90)
-0.8125
(-0.89)
-0.9869
Family social capital
0.1391***
(5.40)
0.1381***
(5.29)
0.1385***
(5.38)
0.1386***
(5.39) 0.1572***
(4.32)
0.1414***
(5.44)
0.1580***
Parental Characteristics:
Parent encourage child
1.8497**
(2.10)
1.8891**
(2.15)
1.8723**
(2.12)
1.8691**
(2.12) 1.6872
(1.37)
1.8494**
(2.09)
1.7609
Happiness score of father
0.0121
(1.13)
0.0130
(1.19)
0.0126
(1.17)
0.0126
(1.17) 0.0140
(0.14)
-0.0103
(-0.46)
0.0018
Parent married
1.0795
(0.64)
1.1474
(0.68)
1.1206
(0.67)
1.1194
(0.67) 2.2144
(0.86)
1.1225
(0.66)
2.4121
Household characteristics
Included
Included
Included
Included
Included
Included
Included
Neighbourhood and Community capital Included
Included
Included
Included
Included
Included
Included
Provinces
Included
Included
Included
Included
Included
Included
Included
Year dummy
Included
Included
Included
Included
Included
Included
Included
N
1,813
1,812
1,813
1,812
1,069
1,813
1,069
Adj. R-squared
0.2101
0.2085
0.2096
0.2096
0.2152
0.2081
0.2142
First-stage
R-squared
0.684
0.028
0.280
0.297
0.033
0.217
0.158
First-stage regression robust F
104.51***
44.82***
6.22***
8.13***
25.53***
8.01**
2.40***
J p-value
0.177
0.219
Notes: z-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01. Durbin-Wu-Hausman chi-square test endogeneity test rejects the null hypothesis that homeownership,
income and father’s happiness is exogenous. J p-value is greater than 5% significance level implying that we do not reject the null hypothesis for the overidentifying restriction test (instruments are valid).
36
(2.00)
(-0.35)
(0.17)
(-2.86)
(6.16)
(0.46)
(-1.41)
(0.72)
(-0.89)
(4.36)
(1.58)
(0.04)
(1.12)
statistics against the null that the excluded instruments are irrelevant in the first-stage
regression is higher than 10, which satisfies the Staiger and Stock (1997) rule of
thumb. These results suggest that father’s education level is a valid instrument. The
results with respect to the relationship between homeownership and SWB are the same
as in column (6) in Table 2.2. As a check on the results in column (2.1), we report the
estimates using the Lewbel (2012) IV alone in column (2.2) of Table 2.5 and the
estimates using the Lewbel (2012) IV and conventional IV together in column (2.3) of
Table 2.5. The coefficient on homeownership in both the columns are positive and
significant and lies between 2.74 to 2.77 percentage points. However, the coefficient
on income remains insignificant.
We use the same three prong strategy to instrument for the happiness score of the
father as we did for family income. In column (3.1) of Table 2.5, we instrument for
the happiness score of the father variable using his job satisfaction score. In column
(3.2), we employ the Lewbel (2012) internal IV alone and in column (3.3) we combine
job satisfaction as the external IV with the Lewbel (2012) internal IV. All the
diagnostics tests suggest that our chosen external instrument is valid and the BreuschPagan test indicates that the heteroskedasticity condition is satisfied as a condition for
using the Lewbel (2012) approach. The coefficient of homeownership in all three
specifications is positive and significant, consistent with the OLS estimates, with
magnitude between 2.33 to 2.79 percentage points. The effect of the happiness score
of the father on SWB of his offspring remains positive, but is insignificant.
In Table A2.4 we present the IV estimates for the effect of homeownership on the
SWB of different subsamples of children, which are very similar to the OLS estimates
in Table 2.3.
As a further test to estimate if differences in SWB of children are due to
homeownership and not to any other pre-existing differences, we use PSM to eliminate
the potential influence of confounding factors. The results using common support of
matching with nearest neighbour, radius, kernel and stratification matching methods
are presented in Table 2.6. The estimates using these various methods of PSM show
that the effect of homeownership on SWB of children is positive and significant. The
37
level of significance of the estimated coefficients are largely consistent with main
results and are in the range 2.64 to 4.27 percentage points.
Table 2.6
Propensity score matching estimates of the average treatment effects
of homeownership on subjective wellbeing of children, CFPS
Variable
Nearest
Neighbour
Matching
Full
homeownership
4.273**
Propensity Score Matching Methods
Radius
Kernel
Stratification
Matching
Matching
2.10 2.646*** 2.59
2.882** 2.25
3.419**
1.99
Notes: t-statistics are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01. The covariates used in generating
propensity scores are age, gender, family income, migrants, type of house and housing tenure with
common support.
While various covariates influencing the SWB of children apart from homeownership
have been controlled for in the regression analysis, one might be worried whether the
sample time period used or the construction of the SWB index is biasing the effect of
homeownership on SWB. One might also be concerned as to whether the effect of
homeownership on SWB has been consistent over the years. To address this issue, we
first reconstruct the SWB index and re-estimate the main model using data from
different combinations of the four waves depending on data availability. We
reconstruct our SWB index by considering only those response items that were
consistently measured over the four waves of CFPS.1 These questions include (1) How
would you rate your academic performance? (2) Do you think you are a good student?
(3) Are you satisfied with your school? (4) Are you satisfied with your Chinese
language teacher? (5) Are you satisfied with your math teacher? Further, we analysed
a small sample of 216 children who were first surveyed in the first wave in 2010 and
then had been subsequently re-surveyed in 2012 and 2014 using the same child
questionnaire.
Using the modified index and controlling for most of the variables used in Table 2.2,
we consistently find a significant and positive effect of homeownership on SWB of
children. The results are presented in Table 2.7. In particular, the results are robust
1
The response items used along with factor loadings and other tests on the properties of this modified
SWB index is presented in appendix Table A2.5. The modified index exhibits satisfactory properties.
38
Table 2.7
Robustness checks, CFPS (4 waves – 2010-2012-2014-2016)
Variables
Full homeownership
(ref: no)
Age
Age
2
Gender (ref: Boys)
1
All waves
0.9893*
(1.72)
2
2012-2014-2016
1.8135**
(2.34)
3
2012-2014
2.2599**
(2.08)
1.1855
(0.81)
-4.1247*
(-1.93)
-5.2281
(-1.58)
(-1.69)
0.1152
(1.34)
0.1648
(1.25)
(-6.95)
-2.1316***
(-5.06)
-1.9265***
-0.0987
*
-2.3081***
Child education
expectation (in years)
0.7141
Ln family income
***
(12.75)
0.6788
-0.1348
(-0.81)
Urban
0.0846
Migrants
-0.3209
Parent encourage child
2.0865
***
***
***
(-3.08)
(8.84)
0.7631
-0.1407
(-0.65)
-0.2198
(-0.67)
(0.15)
0.8804
(1.22)
0.6886
(0.64)
(-0.53)
-0.8069
(-1.07)
-1.2325
(4.34)
2.0489
***
(3.19)
2.5048
**
(6.55)
(-1.12)
(2.45)
Type of house
(ref: Low-rise house)
Apartment
1.1325*
(1.82)
1.5576**
(2.04)
2.1701*
(1.84)
Bungalow
-0.3205
(-0.72)
-0.0158
(-0.03)
0.9815
(1.06)
(2.15)
0.8078
(0.73)
0.4135
(0.27)
**
Quadrangle courtyard
1.6693
Villa
0.6376
(0.37)
2.6198
(1.23)
0.7858
(0.24)
Condominium villa
-0.1352
(-0.04)
-2.2045
(-0.53)
1.8178
(0.50)
Housing tenure: more than
15 years
Received loan for housing
0.1661
(0.39)
-0.0802
(-0.12)
-0.0973
(-0.12)
0.9626
(1.28)
1.3772*
(1.68)
0.6650
(0.49)
0.0962
***
0.0940
***
(7.73)
0.0932
0.0690***
(7.37)
0.0696***
(5.05)
Parent married
1.5478
(0.74)
Happiness score of father
0.0040
(0.32)
Household size
0.1684
(0.60)
Family social capital
Neighbourhood social
capital
Community social capital
Provinces
Yes
Year dummy
Yes
(4.83)
Yes
(6.10)
69.2039
(4.28)
***
(5.59)
Yes
Yes
***
0.1301
***
Yes
***
(5.04)
67.4649***
Constant
57.2148
N
8,600
4,439
1,899
Adj. R-squared
0.0882
0.1538
0.1523
(3.16)
Notes: t-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01. Model 1
included data for all the 4 waves of CFPS but excludes variables that were not collected in year 2010 (family social
capital, neighbourhood social capital, community social capital) and variables that were collected but had missing
data points in year 2016 (parent married, happiness score of father and household size). Hence, regressions have
been estimated including the maximum available data points. Model 1 includes all 4 waves (2010-2012-20142016), model 2 includes 3 waves (2012-2014-2016) while model 3 includes only 2 waves (2012-2014) consistent
with the two waves used in our main model.
39
over the four waves as well as when we use data from fewer waves. We also re-run
the main specification as in column (6) of Table 2.2 over the 2012 and 2014 waves
and find similar effects of homeownership on SWB. The estimates for the control
variables are also largely consistent with the main results. These alternative estimates
suggest that our estimates are not biased to data construction procedures and are
consistent across different waves.
We also extend our analysis to evaluate if the results are robust to variations over time.
Using the modified index and data over 2010, 2012 and 2014 we apply pooled OLS
and panel data regression analysis to estimate the effect of homeownership on the
SWB of children who had been surveyed in the three waves. The main limitation of
using OLS is that unobserved time-invariant heterogeneity is left in the composite
error term. While this may not be a concern if heterogeneity is uncorrelated with the
observed covariates, there is a high chance of serial correlation in the composite error
term when using pooled OLS data across time. Following Tani (2017), we relax the
assumption of orthogonality between time-invariant individual unobserved
heterogeneity and the observed covariates, and use panel random effects estimators.
The Hausman test also fails to reject the null hypothesis that the difference in
coefficients is not systematic, suggesting that the use of the random effects panel
estimator is appropriate. The results using the pooled OLS and random effects
estimator are presented in Table 2.8. The findings of this robustness test provide
further confidence to our earlier results in suggesting that the effect of homeownership
on SWB of children is positive and significant.
Table 2.8 Robustness checks, CFPS (same children surveyed over 2010-2012-2014
waves)
Variables
Full homeownership
Other variables^
N
Pooled OLS
4.2627* (2.45)
*
Include
d648
Random effects Fixed effects
3.8047*
(1.82) 1.8557
(0.69)
Included
Included
648
648
Notes: t-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01.
(^) denotes that family social capital, neighbourhood social capital and community social capital
variables are not included in the regression as they were not available in 2010. Hausman test fails to
reject the null hypothesis (Prob > Chi2 = 0.1694) suggesting that the fixed effect is uncorrelated with all
of the regressors which allows us to conclude that the random effects model rather than the fixed effects
model is appropriate.
40
2.8
Conclusion
There is now a large literature exploring the determinants of adults’, and children’s
SWB, but very little attention has been given to the effect of homeownership on
children’s SWB. We have examined the relationship between homeownership and
children’s SWB in China. We also explored the heterogeneous effect of
homeownership on the SWB of children based on gender, residential location and
migration status of the household. A main takeaway from our results is that the SWB
of children whose parents own their own home is consistently higher than children of
parents who do not own their own home. This result holds for different subgroups and
is robust to a number of checks for endogeneity and alternative ways to split the
sample. A secondary takeaway from our findings is that there are several channels
through which homeownership is related with the SWB of children. Specifically, we
were able to test for, and found support for, four possible channels through which
homeownership influences children’s SWB.
An implication of our results is that government policies to promote full
homeownership with residential property rights should be favoured over renting in
order to realize higher SWB of children. In this respect, our results lend support to the
furtherance of affordable housing programs - such as the Economical and Comfortable
Housing Program and the Housing Provident Fund Program – as ways to promote
homeownership (see e.g. Chen & Deng, 2014; Deng et al., 2011). Our finding that
children who live in houses owned by their parents in urban areas have higher SWB
lends support to Hu and Coulter (2017) who call for greater regulation of the real estate
market in urban China, in order to increase housing affordability and improve
wellbeing of those in urban areas. Our results also support Dietz and Haurin’s (2003)
call for policy intervention to remove discrimination in the housing market, such that
the benefits of homeownership are not illegally denied to minority children. Our
findings are also important for parents wanting to improve the SWB of their children.
They suggest that homeownership provides an important antecedent to doing this.
The mediation results allow us to address the issue of why homeownership matters for
children's subjective well-being. The results from the SEM suggest that parental inputs
into their children’s education, investment in home maintenance, the quality of the
neighbourhood and parents’ emotional support for their children mediate the
41
relationship between homeownership and children’s SWB. These pathways suggest
that homeownership has important spill over effects that enhance the child’s SWB.
One implication of these results is that policies to enhance the pathways might bring
about similar positive effects to homeownership per se. For example, government
investment in improving the quality of neighbourhoods might improve the SWB of
children. Such a suggestion is consistent with studies such as Chetty et al. (2016) who
conclude that better quality neighbourhoods improve outcomes for children later in
life along a range of objective dimensions. In this respect, in 2017 China introduced a
pilot programme in 12 major cities, giving tenants the same access to public services
as homeowners, including the right to enrol their children in their neighbourhood
school districts (Zheng, 2017). Another example, would be to invest in better-quality
non-owner-occupied housing that would replicate the benefits of homeownership in
terms of home physical environment. Some larger cities, such as Shanghai, are
building new rental-only properties with a view to improving the rental market (Zheng,
2017).
Future research should expand on this work by examining the relationship between
homeownership and SWB of children at various age groups across different income
quintiles. Other directions for future research include examining the relationship
between homeownership and SWB of children in other countries, perhaps where
homeownership rates are lower, or examining the relationship between
homeownership and objective outcomes of children, such as performance in school, in
China, for which there are few studies.
There is also scope in the future to explore the role of housing characteristics such as
neighbourhood conditions, dwelling size, sanitation and internet connections as
moderators or mediators of the relationship between homeownership and child
outcomes. This would provide a richer framework for designing appropriately targeted
homeownership policies. Finally, one recent development in urban housing in China
is the redevelopment of shantytowns. Li, Kleinhans and Han (2018) find that while
low-income residents are pleased with the central government’s Shantytown
Redevelopment Projects (SRPs) initiative, they are not content with how these projects
are implemented by local governments. This new development initiative provides an
opportunity to study how the resultant homeownership of these SRPs houses would
42
impact on the SWB of children. It would also be interesting to evaluate how the SWB
of children of those families impacted by the SRPs change over time.
43
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50
APPENDICES
Table A2.1
Factor analysis for the subjective wellbeing items
Item
2012
0.464
0.410
0.598
0.586
0.488
0.511
0.714
0.582
0.665
0.626
3.271
0.327
0.789
0.000
0.767
Academic achievement
Good student
Satisfied with school
Better future
Popular
Easy to get along with
Satisfied with class advisor
Satisfied with foreign language teacher
Satisfied with Chinese language teacher
Satisfied with math teacher
Eigenvalues
Percentage of variance explained
Kaiser-Meyer-Olkin (kmo)
Bartlett test of sphericity (p-value)
Alpha
Factor loadings
2014
0.436
0.428
0.666
0.530
0.459
0.422
0.719
0.598
0.670
0.647
3.228
0.323
0.792
0.000
0.764
Total
0.449
0.420
0.633
0.561
0.475
0.470
0.716
0.589
0.668
0.637
3.250
0.325
0.794
0.000
0.772
Notes: The details of the 10 questions used in this index are given in Table A2. Principle component
analysis method is used with eigenvalues showing that there is one factor. Kaiser-Meyer-Olkin (kmo)
score is used to determine the sampling adequacy and the kmo score is just above 0.78 implies that the
sample is acceptable. The Bartlett test for sphericity which tests if the variables are not inter-correlated
finds that they are not [reject the null hypothesis (p < 0.05)]. The factor loadings of all these four items
are above 0.41 which is fairly acceptable. The Cronbach’s alpha is also moderately high at 0.76 which
shows internal consistency among the variables in the index. The index also explains about a third of
the variances in the sample.
51
Table A2.2
Definition of variables
Variables
Definition of variables
Subjective wellbeing
This variable is constructed by taking an average of 8
questions as validated in Table A1 using factor analysis.
These 8 questions have data in Likert scale on various scales
but were standardised on a 0-100 distribution with 0 rating the
lowest and 100 being the highest wellbeing. These questions
measure subjective judgement on the different aspects of life
by the child. These measures include on Academic
achievement [1. How would you rate your academic
performance], Good student [2. Do you think that you are a
good student?], Satisfied with school [3. Are you satisfied
with your school?], Better future [4. Are you confident about
your future?], Popular [5. Do you think you are popular?],
Easy to get along with [6. Is it easy for you to get along well
with others?], Satisfied with class advisor [7. Are you
satisfied with your class advisor?], Satisfied with foreign
language teacher [8. Are you satisfied with your foreign
language teacher?], Satisfied with Chinese language teacher
[9. Are you satisfied with your Chinese language teacher?],
Satisfied with math teacher [10. Are you satisfied with your
math teacher?].
Homeownership
The household has either full, partial or minor ownership
residential property rights.
Full homeownership
The household has full ownership residential property rights.
No Homeownership
The household does not have full residential property rights
and lives either in homes that are partly owned by family
members or are provided by the work unit including those
who live in public or commercial rental house or with
family/relatives.
Age
Age of the survey respondents measured in years.
Gender
Gender of the survey respondent. (Boys=1; Girls=0)
52
Child education
Highest expectation for child’s own education. The five
expectation
options are converted to corresponding years of schooling as
per CFPS 2017 User Manual as: 1. No school [0 years] 2.
Primary school [6 years] 3. High school [12 years] 4. College
[16 years] 5. Graduate [22 years].
Ln family income
Natural logarithm of total family income.
IHS family income
Inverse hyperbolic since (IHS) transformation of total family
income.
Household size
The number of household members.
Urban
Whether the respondent currently lives in a household that is
in urban residential location. Measured as a dummy variable
with (0) as currently living in rural area and (1) as living in
urban area.
Migrant
Is defined as a respondent living in urban residential location
but having an agricultural/rural hukou. Migrants without a
local urban hukou cannot access the same rights and social
benefits enjoyed by urban residents.
Family social capital
Measures the degree of trust the respondents have on their
parents measured with the question "How much do you trust
your parents?" This question is measured in Likert scale (010) and are standardised on a 0-100 distribution with (0) being
distrustful and (100) being very trustworthy.
Parent encourages
Measures how parents react when the child's test score is
child
lower than expectation. This is denoted as (1) when parents
encourage the child by contacting the teacher, asking the child
to study harder and help the child more while it is denoted (0)
if parents take stricter actions against the child such as
physical punishment, scold the child and ground the child.
Happiness score of
Measures the happiness score of the respondent’s father with
father
the question "How happy are you?" This question is measured
in Likert scale and are standardised on a 0-100 distribution
with (0) very unhappy and (100) being very happy.
53
Education level of
Measures the years of education of the father with conversion
father (years)
scale representing (0 years) Illiterate/Semi-illiterate; (6 years)
Primary school; (9 years) Junior primary school; (12 years)
Senior middle school; (15 years) Junior college; (16 years)
College; (19 years) Master’s degree; and (22 years) Doctoral
degree.
Job satisfaction
Measures the job satisfaction score of the respondent’s father
score of father
with the question "Overall satisfied with the current job" This
question is measured in Likert scale and are standardised on a
0-100 distribution with (0) very unhappy and (100) being very
happy.
Parent married
Measures whether the respondent’s parents are legally
married. This is represented with a dummy value (1) if the
parents are legally married and staying together and (0) if they
are either not married, in cohabitation, divorced or widowed.
Type of house:
Apartment
The household lives in an apartment house type. This is
denoted (1) as living in apartment and (0) as living in other
types of house.
Bungalow
The household lives in a bungalow house type. This is
denoted (1) as living in a bungalow and (0) as living in other
types of house.
Quadrangle
The household lives in a quadrangle courtyard house type.
courtyard
This is denoted (1) as living in a quadrangle courtyard and (0)
as living in other types of house.
Villa
The household lives in a villa house type. This is denoted (1)
as living in a villa and (0) as living in other types of house.
Condominium
The household lives in a condominium villa house type. This
villa
is denoted (1) as living in a condominium villa and (0) as
living in other types of house.
Low-rise house
The household lives in a low-rise house house type. This is
denoted (1) as living in a low-rise house and (0) as living in
other types of house.
54
Housing tenure
Denotes a value of (1) for households living in the same house
for more than 15 years and (0) for those living living in the
same house for less than 15 years.
Received loan for
Denotes a value of (1) for households that received mortgage
housing
loan when purchasing/decorating house and (0) for those who
did not take mortgage loan to acquire housing property.
Neighbourhood
Measures the degree of trust the respondents have on their
social capital
neighbours measured with the question "How happy are
you?" This question is measured in Likert scale (0-10) and are
standardised on a 0-100 distribution with (0) being very
unhappy and (100) being very happy.
Community social
Measures the degree of trust the respondents have on their
capital
local government officials also known as cadre (ganbu)
measured with the question "How much do you trust cadres?"
This question is measured in Likert scale (0-10) and are
standardised on a 0-100 distribution with (0) being distrustful
and (100) being very trustworthy.
Province
25 provinces/municipalities/autonomous regions:
Anhui,
Beijing, Chongqing, Fujian, Gansu, Guangdong, Guangxi,
Guizhou, Hebei, Heilongjiang, Henan, Hubei, Hunan,
Jiangsu, Jiangxi, Jilin, Liaoning, Shaanxi, Shandong,
Shanghai, Shanxi, Sichuan, Tianjin, Yunnan and Zhejiang.
55
Table A2.3 Determinants of subjective wellbeing for children, CFPS (ordered
logit & ordered probit model results)
Variables
Homeownership Status:
Full homeownership (ref: no)
Ordered logit
Ordered probit
0.4140***
(2.96)
0.2374***
(2.99)
-0.5577
(-1.23)
-0.3987
(-1.56)
(1.04)
0.0141
Child personal characteristics
Age
Age
2
0.0190
Gender (ref: Boys)
-0.2530
Child education expectation (in years)
***
(1.38)
***
(-2.97)
-0.1594
(-3.31)
0.1194***
(7.80)
0.0649***
(7.43)
Ln family income
-0.0233
(-0.54)
-0.0108
(-0.43)
Household size
-0.0206
(-0.57)
-0.0107
(-0.57)
Urban
0.0831
(0.59)
0.0807
(0.97)
Migrants
-0.0963
(-0.67)
-0.0763
Household characteristics
Family social capital
0.0220
***
(5.34)
0.0122
***
(-0.92)
(5.73)
Parental Characteristics
Parent encourage child
0.2400*
(1.69)
0.1531**
(2.02)
Happiness score of father
0.0014
(0.81)
0.0010
(1.07)
Parent married
0.1159
(0.40)
0.0862
(0.59)
0.3518**
(2.29)
0.1829**
(2.09)
Bungalow
0.1231
(1.03)
0.0665
(0.97)
Condominium villa
0.0328
(0.15)
-0.0023
(-0.02)
Quadrangle courtyard
0.2588
(0.84)
0.0967
(0.53)
Villa
-0.6620
(-0.69)
-0.3809
(-0.82)
Housing tenure: more than 15 years
-0.0935
(-0.89)
-0.0225
(-0.38)
Received loan for housing
0.1524
(0.85)
0.0722
(0.71)
0.0173***
(7.46)
0.0102***
(7.90)
(6.68)
***
(6.20)
Household characteristics
Type of house (Ref: Low-rise house)
Apartment
Neighbourhood and Community capital
Neighbourhood social capital
***
Community social capital
0.0125
0.0066
Province
Yes
Yes
Year dummy
Yes
Yes
N
1,813
1,813
Notes: t-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01.
56
Table A2.4
Determinants of subjective wellbeing in sub-samples, CFPS (IV results)
Variables
Homeownership Status:
Full homeownership (ref: no)
Child personal characteristics:
Age
Age2
Gender (ref: Boys)
Child education expectation (in years)
Household characteristics:
Ln family income
Household size
Urban
Migrants
Family social capital
Parental Characteristics:
Parent encourage child
Happiness score of father
Parent married
Household Housing characteristics:
Type of house (Ref: Low-rise house)
Apartment
Bungalow
Condominium villa
Quadrangle courtyard
Villa
Housing tenure: more than 15 years
Received loan for housing
Neighbourhood and Community capital:
Neighbourhood social capital
Community social capital
Province
Year dummy
Constant
N
Adj. R-squared
First stage
R-squared
First-stage regression robust F
Boys
Girls
TSLS regression with Lewbel (2012) IV for sub-samples for:
Urban
Rural
Locals
Migrants
4.1808***
(2.99)
1.7028
(1.08)
2.4084*
(1.77)
2.4773
(1.36)
2.8262**
(2.18)
2.3797
(1.47)
-5.4565
0.2024
(-1.40)
(1.30)
-2.8884
0.0889
(-0.71)
(0.55)
0.9126***
(7.40)
0.5206***
(3.76)
-0.0828
-0.0168
-0.6713
0.6769***
(-0.02)
(-0.11)
(-0.83)
(4.74)
-5.6530
0.2042
-2.7532***
0.7998***
(-1.43)
(1.29)
(-3.83)
(6.64)
-1.9979
0.0585
-2.1538***
0.7023***
(-0.60)
(0.44)
(-3.56)
(6.85)
-8.3362
0.3158
-0.7448
0.8073***
(-1.57)
(1.49)
(-0.67)
(3.98)
-0.3280
0.0007
2.9005**
-1.6242
0.1250***
(-0.87)
(0.00)
(2.16)
(-1.23)
(3.81)
0.2234
-0.2364
-1.0030
-0.2143
0.1748***
(0.57)
(-0.94)
(-0.88)
(-0.18)
(4.18)
0.6928
-0.1249
(1.54)
(-0.43)
-0.4798
-0.1606
(-1.36)
(-0.55)
-0.4262
-0.0707
0.8521
(-1.33)
(-0.30)
(0.84)
0.8211
-0.3106
(1.45)
(-0.72)
-0.6338
0.1356***
(-0.67)
(3.92)
0.1380***
(3.58)
0.1489***
(4.68)
0.1114***
(2.61)
1.8726
0.0232
2.9294
(1.56)
(1.52)
(1.21)
1.9324
0.0076
-0.6153
(1.53)
(0.53)
(-0.28)
1.6316
-0.0015
-2.1293
(1.26)
(-0.09)
(-0.90)
2.1105*
0.0265*
3.0817
(1.84)
(1.84)
(1.29)
2.0883**
0.0097
2.8206
(2.02)
(0.77)
(1.46)
0.6951
0.0245
-4.3084
(0.43)
(1.18)
(-1.33)
1.3091
0.8062
-1.4444
0.4118
-0.6276
-1.0239
-0.5286
(0.99)
(0.76)
(-0.28)
(0.21)
(-0.21)
(-1.07)
(-0.32)
2.8803**
0.3815
-5.7713
-0.1629
1.0122
0.7984
1.7367
(2.16)
(0.35)
(-0.84)
(-0.09)
(0.34)
(0.93)
(1.21)
1.7143
1.1865
5.3814***
3.2985*
1.2444
0.1300
1.2010
(1.52)
(1.00)
(2.74)
(1.80)
(0.45)
(0.12)
(0.88)
2.9669
0.1124
-12.9790***
-1.5595
4.5330**
-0.4030
0.1507
(1.30)
(0.10)
(-8.48)
(-0.88)
(2.43)
(-0.46)
(0.08)
2.8401**
0.2912
-2.5145
-0.8529
1.3149
-0.2154
0.4543
(2.42)
(0.31)
(-0.43)
(-0.55)
(0.62)
(-0.29)
(0.35)
-0.5701
1.0959
(-0.33)
(0.75)
2.7966
3.4046
-0.9830
1.4410
(1.21)
(0.55)
(-0.70)
(0.60)
0.1134***
0.0801***
Yes
Yes
56.9005**
973
0.2099
(5.93)
(5.01)
0.1167***
0.0707***
Yes
Yes
51.0381**
840
0.1854
(5.27)
(4.03)
0.1168***
0.0633***
Yes
Yes
26.9532
827
0.2198
(5.61)
(3.86)
0.1136*** (5.59)
0.0862*** (5.28)
Yes
Yes
69.0615*** (2.74)
986
0.2096
0.1138***
0.0790***
Yes
Yes
45.2803**
1,385
0.2047
(6.56)
(5.82)
0.1110***
0.0668***
Yes
Yes
77.6564**
428
0.2151
(4.08)
(2.86)
0.921
173.36***
0.781
60.65***
0.737
73.12***
(2.32)
(1.97)
0.784
59.65***
0.609
16.45***
(1.05)
(2.13)
0.797
48.23***
Notes: z-statistics clustered at household level are in parenthesis; * p < 0.10, ** p < 0.05, *** p < 0.01. Durbin-Wu-Hausman chi-square test endogeneity test rejects the null hypothesis that homeownership is
exogenous
57
(2.30)
Table A2.5
Factor analysis for the subjective wellbeing items (as used in
robustness tests)
Factor loadings
Item
Academic achievement
Good student
2010
2012
2014
2016
Total
0.606
0.598
0.561
0.492
0.547
0.517
0.542
0.507
0.569
0.533
Satisfied with school
0.677
0.690
0.704
0.708
0.693
Satisfied with Chinese language 0.669
teacher
Satisfied with math teacher
0.656
0.689
0.696
0.684
0.684
0.675
0.697
0.695
0.679
Eigenvalues
Percentage of variance explained
2.064
0.412
1.966
0.393
2.033
0.406
2.006
0.401
2.020
0.404
Kaiser-Meyer-Olkin (kmo)
0.667
0.637
0.656
0.654
0.655
Bartlett test of sphericity (p- 0.000
value)
Alpha
0.644
0.000
0.000
0.000
0.000
0.614
0.633
0.624
0.631
Notes: These 4 questions include measures on Academic achievement [1. How would you rate your
academic performance], Good student [2. How good a student do you think you are?], Satisfied with
school [3. Are you satisfied with your school?], Satisfied Chinese language teacher [4. Are you satisfied
with your Chinese language teacher?], Satisfied math teacher [5. Are you satisfied with your math
teacher?].
58
CHAPTER 3
HOUSING WEALTH AND
HAPPINESS IN URBAN CHINA
This chapter presents co-authored work with Russell Smyth, Zhiming Cheng and
Haining Wang. The chapter uses data from China Household Finance Survey (CHFS)
administered by Southwestern University of Finance and Economics. The authors
would like to thank three anonymous referees of Cities for insightful comments on an
earlier version that greatly improved the paper.
59
Abstract
China has experienced rapid growth in inequality in housing wealth. We examine how
housing wealth and housing wealth inequality are associated with happiness, drawing
on panel data from three waves of the China Household Finance Survey (CHFS). We
find that housing wealth and housing wealth inequality matter for happiness. More
housing wealth increases happiness with diminishing returns to owning a second and
third house. The relationship between housing wealth inequality and happiness
depends on the reference group and the level of housing wealth inequality. An increase
in housing wealth inequality among individuals of the same gender and similar age
and education who live in the same city as me provides a signal that I also could
accumulate housing wealth and this prospect makes me happier up to a threshold.
However, once housing wealth inequality passes that threshold, this lowers my
happiness because the wealth of those toward the top of the distribution seems out of
reach. Similarly, a general increase in housing wealth inequality across the province
in which I live lowers my happiness, which is consistent with a jealousy or status
effect. We also employ the concentration index (CI) to examine the effect of housing
wealth inequality on happiness inequality. The wealth-related CIs for happiness are all
positive, suggesting that higher happiness is more concentrated among people with
higher housing wealth.
60
3.1
Introduction
Piketty’s (2014) Capital in the Twenty-First Century has put an academic spotlight on
the role that inequality in housing wealth has played in contributing to steadily rising
inequality in many economies since the 1970s and 1980s. Recent institutional and
socioeconomic developments have reinforced the importance of housing wealth across
many economies, including an increased role of homeownership and commodification
of housing wealth, even in economies in which housing markets have traditionally
been less important (Arundel, 2017). Yet, despite the growing importance of housing
wealth inequality, the housing wealth dimension is not well understood in the
international housing literature. Recently, studies such as Dorling (2014) and Arundel
(2017) have called for much closer attention to be given to the role of housing wealth
inequality in the housing and urban environment literature. We respond to this call by
examining how housing wealth inequality affects people’s happiness.
To do so, we situate our study in urban China. Urban China is an excellent illustration
of a society in which housing markets were traditionally not important, but the
commodification of housing and rapid growth in home ownership over the last three
decades has created massive housing wealth inequality. The housing reforms, which
commenced in 1988, have transformed the former socialist housing allocation system
into a housing market. As a result, there has been a large increase in housing prices.
House prices increased by over 10 per cent per year in real terms between 2003 and
2014 (Glaeser et al., 2017) and have been growing nearly twice as fast as national
income (Chen & Wen, 2017). Approximately 80 per cent of urban households own
their houses and housing assets account for nearly 80 per cent of household wealth,
which is much higher than in most other countries (Xie & Jin, 2015).
One reason for rising housing wealth inequality is that a high proportion of houses in
the private sector that were previously public rental housing were sold with subsidies
to sitting tenants. Hence, those with political connections and resourceful work units
initially benefited the most during the privatization process (Yi & Huang, 2014).
Housing inequality is also intergenerational. While urban China’s older population
benefitted most from the windfalls during the housing reforms (Park & Shen, 2015),
first generation low-income households struggle to get a foothold in the housing
market, which affects the starting point for the social mobility of the next generation
61
(Ren & Hu, 2016). There is also substantial variation in housing wealth inequality
across provinces. Figure 3.1 shows that the Gini coefficients in the central and western
regions are relatively higher than that in the eastern region in 2015, based on the China
Household Finance Survey (CHFS) data used in this study.
Figure 3.1
Housing wealth inequality by province in 2015
Source: 2015 China Household Finance Survey
As a consequence of the housing reforms, a social and spatial sorting of households
and neighbourhoods is emerging with significant residential segregation (Huang &
Jiang, 2009). Big cities, such as Beijing and Shanghai, have seen the creation of highend luxury neighbourhoods sitting alongside poor communities (Ko, 2017). It has been
reported that 15 per cent of households own multiple properties (Ren & Hu, 2016)
with some wealthy individuals owning much more. Some individuals in Beijing and
Shanghai own more than 100 condominium units (Murayama, 2016). Many of these
condominiums are unoccupied with the residential vacancy rate in Chinese cities
higher than in major US cities (Holdstock, 2017). Yet, low income households, often
referred to as the ‘low end population’, depend on cheap housing options, such as
illegal rental properties (Chen, 2018).
62
We use the 2011, 2013 and 2015 waves of CHFS to examine how housing wealth and
inequality in housing wealth is related to happiness. We include not only current
residence but also other houses the respondent may own in calculating total house
wealth. We also examine whether housing wealth inequality contributes to differences
in happiness within reference groups, as well as employing the concentration index
(CI) to analyse housing wealth-related inequality in happiness. We find that higher
happiness is more concentrated among people with more housing wealth (measured
by total house value).
Our study extends the emerging literature on the relationship between consumption or
wealth inequality – rather than just income alone – and happiness in China (Cheng et
al., 2018; Cheng et al., 2016; Lei et al., 2018; Wang et al., 2019a, 2019b) to focus on
the roles of housing wealth inequality. The relationship between housing wealth
inequality and happiness is important for various reasons. One is that housing wealth
inequality in China is becoming increasingly visible (Chen, 2018). Hence, a study such
as this speaks directly to spatial comparisons, which have been shown to be important
for happiness (Buttrick et al., 2017; Huang, 2018). Second, there is widespread
recognition that an uneven distribution of wealth has the potential to be a source of
social conflict and increases the risk of instability (Li et al., 2008). This potentially
extends to housing wealth inequality with the Chinese government increasingly
concerned about the implications of residential segregation for social unrest (Ko, 2017;
Murayama, 2016). This is particularly important given that housing wealth inequality
is a major cause of wealth inequality in China. Housing wealth contributed to 63 per
cent of overall household wealth inequality in 2002 (Li & Wan, 2015). This figure
increased to 76 per cent by 2012 (Xie & Jin, 2015). Third, inequality in housing wealth
also has broader socio-economic implications. For example, Wei and Zhang (2011)
show that housing wealth is linked to the ability of young males to find a marriage
partner.
3.2
Literature review
Housing inequality in China has been extensively studied in terms of housing
conditions and facilities, number of houses owned, housing prices and the housing
price-income ratio (Huang & Li, 2014; Yi & Huang, 2014). At the same time, a large
literature has evolved on the factors correlated with happiness in China (see eg.
63
Appleton & Song, 2008; Asadullah et al., 2018; Cheng, 2014; Cheng et al., 2017;
Cheng & Smyth, 2015a, 2015b, 2017; Cheng et al., 2015; Cheng et al., 2014; Knight
& Gunatilaka, 2012; Knight et al., 2009; Li et al., 2018a; Li et al., 2018b; Mishra et
al., 2014; Tani, 2017; Wang & Cheng, 2017; Wang et al., 2019a; Wang et al., 2017).
A smaller subset of this literature examines the relationship between housing and
happiness. Studies find that happiness is correlated with homeownership (Hu, 2013);
housing conditions (Zhang et al., 2018); living space (Hu & Coulter, 2017) and
housing stress and disadvanatge among rural-urban migrants (Li & Liu, 2018). Cheng
et al. (2016) develop a theoretical model that shows how a gradient of housing property
rights related to happiness in China and test the predictions of the theoretical model
using data from the 2011 CHFS, which is the first wave of the dataset used in the
present study.
We extend this literature to examine how housing wealth inequality affects happiness
in China. The two closest studies to ours are Li et al. (2015) and Zhang and Zhang
(2019). Li et al. (2015) use the first two waves of CHFS to examine how housing
wealth, as one component of overall household wealth, affects happiness. Li et al.
(2015) find that housing as an asset, along with other household assets, is positively
correlated with happiness and that happiness increases with the average assets of the
community in which one lives (i.e. there is a signalling effect). We differ from Li et
al. (2015) in that our focus is on housing wealth inequality. Using cross-sectional data
from 2011 CHFS, Zhang and Zhang (2019) find that the appreciation in value of one’s
home residence, relative to original purchase price, is positively correlated with
happiness. We differ from Zhang and Zhang (2019) in that we use panel data
regression to examine the relationship between time-variant within-household housing
wealth change and happiness, net of effects of time-invariant unobservables (e.g. timeinvariant risk preference, social capital and personality) that may bias the estimates.
To summarize, while there is growing international interest in housing wealth
inequality as a contributor to overall wealth inequality following Piketty’s (2014)
tome, there are no existing studies for China, or other countries, that examine how
housing wealth inequality affect happiness, employing panel data, which is what we
seek to do in the current study.
64
3.3
How does housing wealth of others affect happiness in Chinese cities?
We assume interdependent preferences in which one’s utility depends not only on
one’s housing wealth, but also a combination of one’s housing wealth and the housing
wealth of relevant others. Following Hirschman and Rothschild (1973) and Senik
(2008) assume a simplified society in which there are only two individuals (or groups
of individuals): A and B.
Let A’s happiness (HAPPA) depends on her own housing wealth (HWA), her expected
housing wealth (EA) and, in part, the observed housing wealth of B (HWB). A’s
happiness function is then HAPPA = V(HWA, EA(HWB), HWB). The signs on V/ HWA
and V/EA are positive, but the sign on the partial derivative V/HWB is ambiguous.
Specifically, V/HWB= [(V/EA)( EA/EB)] + V3. The term (V/EA)( EA/EB)
represents the information effect of B’s housing wealth (HWB) on A’s happiness
(HAPPA) and is positive. The term V3 represents the comparison effect and captures
the direct effect of HWB on V. The sign on V3 depends on whether an increase in B’s
housing wealth generates a signalling effect, in which case it will be positive, or a
jealousy/status effect, in which case the sign will be negative. Overall, the sign on
V/HWB, hence, depends on the relative strength of the information and comparison
effects. The sign on V/HWB will be positive if the signalling effect dominates or, if
the status effect dominates, but the information effect outweighs the comparison effect.
Whether the signalling or jealousy/status effects dominate is a direct function of the
extent to which A feels that she can emulate the success of B in accumulating housing
wealth. This, in turn, is a function of two factors. The first is the extent to which the
environment is more mobile and uncertain (Hirschman & Rothschild, 1973). The
signalling effect is likely to be more important in societies in which the environment
is uncertain and there are greater opportunities for upward social mobility (Senik,
2008). The second is the extent to which B’s characteristics, in terms of ability to
accumulate housing wealth, are similar to A. In this respect, an uncertain environment
in which there are opportunities for upward social mobility are a necessary, but not
sufficient, condition for the signalling effect to dominate. If the conditions under which
A can potentially emulate the success of B do not exist, A has no prospect to
accumulate housing wealth. But, even if opportunities for upward social mobility exist,
65
this does not mean that everybody will be upwardly social mobile. Indeed, in fast
moving uncertain environments, such as China, in which some people get ahead,
others will be left behind, widening inequalities in housing wealth accumulation. And,
if opportunities for upward social mobility exist in general, whether A thinks that she
will be well-placed to take advantage of them, will depend on whether B, who she sees
accumulating housing wealth, has similar attributes to her. If A observes B
accumulating housing wealth and B has similar attributes to A, A will feel that she can
emulate B’s success.
How important do we expect the signalling and jealousy/status effects to be in China,
relative to the West? China differs from the West in the following salient respects.
First, as a post-socialist transition society, its environment is more mobile and unstable
than established western democracies. This implies that there is greater potential for
more rapid housing wealth accumulation for those with the right attributes. Second,
greater inequalities in housing wealth will be created within a shorter period. The
combination of these factors means that, essentially, we expect the two effects to be
more stark, relative to what one would observe in established western democracies.
On the one hand, when we observe others with very similar characteristics to us
accumulating wealth, we expect to see a stronger signalling effect than in the West.
The reason is that the greater opportunities for upward social mobility create greater
potential for one to accumulate housing wealth more quickly than in the West,
generating welfare-enhancing ‘anticipatory feelings’ (Caplin & Leahy, 2001). At the
same time, if I do not have the same, or similar, characteristics as those whom I observe
accumulating housing wealth, that I feel will enable me to emulate their success, I am
likely to experience a stronger jealousy effect than in the West because the resulting
gap generated by others getting richer is likely to be larger. This might be reinforced
in the Chinese case if I feel that in creating the mobile and uncertain environment in
which others accumulate housing wealth, the government no longer cares about those
with my characteristics. This is likely to be particularly true for certain groups that
benefitted from socialist housing allocation in urban China prior to 1988, but do not
have the skills to adapt to, and thrive in, the mobile and uncertain environment that
characterises post-Mao China.
66
3.4
Data and methods
We use data from the 2011, 2013 and 2015 waves of the CHFS, administrated by the
Southwestern University of Finance and Economics in China (Gan et al., 2014). The
CHFS collects information on individual, household and community characteristics. It
employs a stratified three-stage probability proportion to size (PPS) random sampling
design weighted by population size in each stage. In the first stage, 80 counties
(including county-level cities and districts) were selected from 2585 primary sampling
units (PSUs) from all provinces and municipalities in China. In the second stage four
urban neighbourhood committees or rural villages were selected from each PSU from
the first stage. In the third stage 20-50 households (depending on the levels of
urbanisation and economic development) were selected from each neighbourhood
committee or village chosen in the second stage. The 2011 baseline data covers 8,438
households and 29,324 individuals from 320 communities across 25 mainland
provinces. In 2013 and 2015 households were re-surveyed. New households were also
surveyed. The sampling framework covers 29 mainland provinces and municipalities.
The 2013 wave covers 28,141 households and 97,906 individuals and the 2015 wave
covers 37,289 households and 133,183 individuals. Given the fact that migrants face
formidable institutional and economic barriers in pursuing home ownership in urban
China due to their hukou status and other restrictions (Chen et al., 2011), we restrict
our sample to urban locals in this study. In total, there are 4,576 individuals in the 2011
wave, 16,665 individuals in the 2013 wave and 20,968 individuals in the 2015 wave
in our analytical sample.
We use a two-way fixed effects panel regression model that controls for both
individual and time fixed effects to examine the relationship between housing wealth
and individual happiness. The individual fixed effects allow us to eliminate the
influence of unobserved time-invariant individual characteristics, such as optimism,
resilience and intelligence, while the time fixed effects allow us to eliminate the effects
of unobserved time-varying characteristics common to all individuals, such as
economic and housing market growth, on happiness.9
9
Note that 2011-2015 CHFS data is an unbalanced panel data in which some individuals were observed
only once (e.g. new survey respondents in each wave or respondents who left the survey after one wave
and did not re-join the survey thereafter). The fixed effects estimator can be applied with unbalanced
panel data (Semykina & Wooldridge, 2010). In fixed effects linear regression, cross-sectional singleton
observations are included in the model to estimate the constant term and panel-level effect, but they
67
The happiness function is as follows:
𝐻𝑎𝑝𝑝𝑖𝑛𝑒𝑠𝑠it = 𝛼 + 𝛽𝐼𝑛𝑒𝑞𝑢𝑎𝑙𝑖𝑡 + 𝛾𝐻𝑜𝑢𝑠𝑒𝑖𝑡 + 𝛿𝑊𝑒𝑎𝑙𝑡ℎ𝑖𝑡 + 𝜃𝐷𝑒𝑏𝑡𝑖𝑡 +
𝜌𝐻𝐻𝑖𝑛𝑐𝑖𝑡 + 𝜑𝑋𝑖𝑡 + 𝜇𝑖 + 𝜎𝑡 + 𝜀𝑖𝑡
(3.1)
where subscript i denotes the individual and t represents the specific wave of the
survey.
Happinessit is measured, on a five-point scale ranging from 1 (very dissatisfied) to 5
(very satisfied), by the response to the survey question: Are you satisfied with your
life? Only one adult member in each household answered this question.
Inequalit is housing wealth inequality measured by the Gini coefficient or Theil index
within the individual’s reference group, defined by city of residence, gender, age and
education.10 Following the literature (Clark et al., 2008; Huang et al., 2016; Oshio et
al., 2011; Wang et al., 2019a), reference groups are first defined at the city level.
Within each city, further reference groups are constructed along the three dimensions
of gender, age and education. Age is divided into six categories: younger than 20, 2029, 30-39, 40-49, 50-59, and 60 or above. Education is divided into three categories
according to the years of education one received: primary school and below (0-6
years), high school (9-12 years) and college or above (15 years or more). Therefore,
there are thirty-six reference groups in total within each city (2×6×3=36).
The Gini coefficient measures the degree of wealth equality. The Gini coefficient can
vary from zero (perfect equality) to one (perfect inequality). A Gini coefficient of zero
means that every household has the same housing wealth, while a coefficient of one
indicates that a single household possesses all the housing wealth. The Theil index
measures the entropic distance that the population is away from an egalitarian state, in
play no role in estimating the coefficients and standard errors for independent variables. The identifying
assumption of fixed effects is that unobservable factors that might simultaneously affect the dependent
and independent variable of the regression are time-invariant. Fixed effects estimation exploits withinindividual variation over time. Across-individual variation is not used to estimate the regression
coefficients because this variation might reflect omitted variable bias. In other words, including
singleton observations in fixed effects regression will not bias the results because the identifying
assumption of the fixed effects estimator does not rely on the singleton observations.
10
To provide a point of comparison, we also provide results for the Gini coefficient and Theil index,
defined at the province and city levels, in later analysis (models 1 and 2 of Table 2 and Table A3).
68
which every household has the same housing wealth. A Theil index of zero indicates
perfect equality, in which every household has an equal proportion of housing wealth
in the population, while a Theil index of one represents perfect inequality. The Gini
coefficient is relatively more sensitive to changes in the middle of the wealth
distribution, while the Theil index is relatively more sensitive to changes that affect
the upper tail of the wealth distribution (Atkinson & Bourguignon, 2015; Gastwirth,
2017).
Houseit is the total amount of housing wealth. Wealthit is the total amount of other
categories of household wealth, excluding housing wealth. Wealthit includes financial
wealth (e.g. social insurance account balance, cash, savings, stocks, funds, bonds, gold
and non-RMB assets) and non-financial wealth (e.g. agricultural productive assets,
business assets, land and vehicles). Debtit is the total amount of formal and informal
household debt. HHincit is the total amount of annual household income, including
wages, agricultrual production income, business income, investment income and
tansfers. All categories of household wealth, debt and income have been deflated by
the consumer price index (CPI), using 2011 as the base year, and were transformed
into natural logarithms prior to analysis. Since some households may have a zero value
for one or more proxies of debt or wealth, we add one to the amount of each wealth or
debt measure prior to transforming that measure into its natural logarithm.
Xit is a vector of control variables that the existing literature suggests are correlated
with happiness; namely, age, gender, marital status, education, health status, degree of
risk aversion, job status, whether the respondent has medical insurance, whether the
respondent has superannuation, family size, number of children and the province in
which the respondent resides. Appendix Table A3.1 contains definitions and
descriptive statistics for each of the control variables. Of the remaining variables, μi is
the individual fixed effect; σt is the time (wave) fixed effect; and εit is the error term.11
In equation (3.1) we include a rich set of observed control variables and employ twoway fixed effects regression. However, there may exist unobservables that bias the
11
We tested for multi-collinearity between the variables in Equation (3.1) using pairwise correlations
and variance inflation factors. The results, which are available on request, suggest multi-collinearity is
not a problem.
69
relationship between happiness and housing wealth and its inequality. To address this,
we employ an approach proposed by Oster (2019) to evaluate whether, and to what
extent, our results suffer from omitted variables bias. Oster (2019) argues that
movements in both coefficient and R-squared should be considered when evaluating
whether omitted variable bias is present. Oster (2019) extends the methodology for
analysing coefficient stability under the assumption that the relationship between
treatment and unobservables can be recovered from the relationship between the
treatment and observables. Oster (2019) proposes two approaches to evaluate
robustness to omitted variable bias. One approach is to assume a value for Rmax and
calculate the value of δ for which the treatment effect equals zero. Rmax is R-squared
from a hypothetical regression of the outcome on treatment and both observed and
unobserved controls. A value of 𝑅𝑚𝑎𝑥 = 1.3𝑅̃ is suggested to estimate a bias-adjusted
treatment effect bound (𝑅̃ is R-squared from the regression with controls). A value of
δ can be interpreted as the degree of selection on unobservables, relative to
observables, that would be necessary to explain away the result. The value of δ which
produces β=0 with 𝑅𝑚𝑎𝑥 = 1.3𝑅̃ should exceed one.
Another approach is to use bounds on Rmax and δ to develop a set of bounds for the
treatment effect, [𝛽̃, 𝛽 ∗ (min{1.3𝑅̃ , 1} , 1)], in which 𝛽̃ is estimated with 𝑅𝑚𝑎𝑥 = 𝑅̃
and δ=0 in the regression with controls, 𝛽 ∗ is the bias-adjusted treatment effect
estimated with 𝑅𝑚𝑎𝑥 = min(1.3𝑅̃ , 1) and δ=1 in the full model. There are two
standards for robustness. First, in cases in which the inclusion of controls moves the
coefficient toward zero, the identified set should not include zero. Second, the
identified set should fall within +/-2.8 standard errors of the controlled estimate, which
is the bounds of the 99.5 per cent confidence interval. This standard represents a test
of whether the magnitude of the estimate in the regression with controls is similar to
the bias-adjusted estimate. This standard is also applicable to those cases in which
adding the controls moves the coefficient away from zero.
Table 3.1 presents summary statistics on the measures of happiness, housing wealth
and inequality in housing wealth defined at the city-gender-age-education level. The
mean happiness score increased slightly from 3.73 to 3.74 between 2011 and 2015, but
was only 3.66 in 2013. The modest increase in happiness levels in recent years is
70
consistent with the trends observed in China (Asadullah et al., 2018; Easterlin et al.,
2012). In the CHFS sample, 73.88 per cent of households owned one house, 12.93 per
cent of households owned two houses and 2.01 per cent of households reported owning
three houses.12 Total housing wealth in logs increased from 11.18 in 2011 to 11.67 in
2015. The wealth of the first house accounts for the largest proportion, being
responsible for more than 98 per cent of total housing wealth. Results of a MANOVA
test (W=0.9986, p=0.0000) indicate that there are significant differences in housing
wealth structures across the three waves. Both the Gini coefficient and Theil index
show that there was a sharp increase in housing wealth inequality within the citygender-age-education defined reference group between 2011 and 2015. The Gini
coefficient increased from 0.36 to 0.41 across the three waves and the Theil index
increased from 0.31 to 0.37.13
Table 3.1
Summary statistics of key variables, China Household Finance
Survey 2011-2015
2011
Mean
Happiness
2013
Std. Dev. Mean
2015
Std. Dev. Mean
Std. Dev.
3.73
0.81
3.66
0.85
3.74
0.83
Housing wealth
11.18
4.23
11.14
4.52
11.67
3.94
Wealth of 1st house
11.05
4.19
10.95
4.52
11.49
3.94
Wealth of 2nd house
1.99
4.60
1.94
4.60
1.92
4.61
Wealth of 3rd house
0.26
1.82
0.29
1.93
0.26
1.85
Gini coefficient
0.36
0.17
0.39
0.18
0.41
0.16
Theil index
0.31
0.25
0.36
0.25
0.37
0.25
We employ a regression-based decomposition analysis of the CI to capture the
contribution of housing wealth inequality to happiness inequality. The CI is calculated
based on the concentration curve, which plots the cumulative proportion of happiness
against the cumulative proportion of the sample, ranked according to housing wealth,
12
Hence, the percentage of households owning two or three houses (14.94 per cent) accords with the
statement that 15 per cent of households own multiple properties (Ren & Hu, 2016) cited in the
introduction.
13
For the full sample, the overall Gini coefficient for total housing wealth is 0.64. The decomposition
of this Gini coefficient shows that the first house is the biggest contributor to overall housing wealth
inequality, accounting for 74.88 per cent, while the contributions of the second and third houses are
only 18.33 and 3.58 per cent, respectively (see Appendix Table A3.2 for full results).
71
beginning with the person with least wealth (see Figure 3.2). The CI is defined as twice
the area between the concentration curve and the line of equality (the diagonal), and
for happiness, it can be expressed as follows:
𝐶𝐼 =
2
𝑛𝜇
∑𝑛𝑖=1 ℎ𝑎𝑝𝑝𝑖𝑛𝑒𝑠𝑠𝑖 × 𝑅𝑖 − 1
(3.2)
where n is the size of the population, µ is the mean of happiness, and Ri is the fractional
rank of individuals by housing wealth. CI takes a value of zero when there is no
housing wealth-related happiness inequality. In the case in which happiness is higher,
a positive (negative) CI indicates that higher happiness is more concentrated among
people with higher (lower) wealth. The larger the absolute value of CI, the greater the
degree of happiness inequality. Because the measure of happiness in this study is a
bounded variable, we adopt the normalized concentration indices proposed by
Erreygers (2009), which are based on the standardized version of the variable of
interest and, hence, are scale invariant.
1
Concentration curve for housing wealth-related happiness
.2
.4
.6
.8
concentration curve
0
Figure 3.2
0
.2
.4
.6
cumulative proportion of population
ranked by housing wealth
72
.8
1
Given the relationship between happiness and the various explanatory factors in
Equation (3.1), the CI for happiness can be decomposed as:
𝐶𝐼 = ∑𝑘(𝛽𝑘 𝑥̅𝑘 /𝜇)𝐶𝐼𝑘 + 𝐺𝐶𝜀 /𝜇
(3.3)
where βk is the estimated coefficients in Equation (1), 𝑥̅𝑘 is the mean of determinant
𝑥𝑘 and µ is mean happiness. CIk is the concentration index for determinant 𝑥𝑘 , which
is defined analogously to CI. 𝐺𝐶𝜀 is a generalized concentration index for the residual
2
𝜀𝑖 , which is defined as 𝐺𝐶𝜀 = ∑𝑛𝑖=1 𝜀𝑖 𝑅𝑖 . The CI can be decomposed into the
𝑛
explained component, which measures the contribution of determinants, and the
unexplained component.
3.5
Main results
Table 3.2 presents the fixed effects estimates for the Gini coefficient and Theil index.
We include a full set of controls as specified in Appendix A3.1 as well as wave fixed
effects.
We first examine the relationship between provincial housing wealth inequality and
happiness. In Models 1 and 2 we construct a Gini coefficient and Theil index for
housing wealth inequality at the province level and examine their impact on happiness.
The results show that provincial housing wealth inequality has a significant, and
negative, effect on an individual’s happiness. This result suggests a jealousy or status
effect and is in line with findings in studies that have found a negative association
between happiness and income inequality in urban China, usually when income
inequality is measured by the Gini coefficient in a broad geographical area, such as
province (Huang, 2018; Smyth & Qian, 2008; Wu & Li, 2017).
In models 3 and 4 we examine the relationship between happiness and housing wealth
inequality using a city-gender-age-education defined reference group. People of the
same age, education and gender living in the same city are likely to be a much more
relevant reference group, than all people living in the same province. The results in
models 3 and 4 show that both measures of housing wealth inequality are positive and
significant, suggesting that the increase in housing wealth inequality experienced in
73
Table 3.2
Reference
group
Gini
Fixed effects estimates of housing wealth and housing wealth
inequality on happiness
Province
0.0069*** 0.0069***
City-gender-ageCity-gender-ageeducation
education
(3)
(4)
(5)
(6)
***
0.1201
0.1414
(3.27)
(1.35)
0.0668***
0.1799***
(2.91)
(3.53)
-0.0306
(-0.21)
-0.1110**
(-2.57)
***
***
***
0.0078
0.0079
0.0078
0.0080***
(4.00)
38,299
0.0386
(5.00)
38,299
0.0387
(1)
-0.4917**
(-2.48)
(2)
-0.2960***
(-3.54)
Theil
Gini2
Theil2
Housing
wealth
N
adj. R2
(3.93)
38,299
0.0390
(5.02)
38,299
0.0386
(4.96)
38,299
0.0387
(5.05)
38,299
0.0389
Notes: t statistics in parentheses; * p < 0.10, ** p < 0.05, *** p < 0.01; all specifications control for a full
set of controls as specified in Appendix Table A1 as well as wave fixed effects; full results are available
from the authors.
recent years has improved an individual’s happiness. Model 3 shows that a standard
deviation increase in the Gini coefficient (a 0.17 increase) is associated with an
increase in the happiness score of 0.02 points, which corresponds to an increase of
2.41 per cent standard deviations. The effect size of the Theil index is very similar.
Model 4 shows that a one standard deviation increase in the Theil index (a 0.25
increase) is associated with a 0.017-point increase in the happiness score.
The reason for the different signs on income inequality between Models 1 & 2 and 3
& 4, relate to how the reference group is defined. When an individual observes an
increase in housing wealth inequality at the province level, this generates a jealousy
effect because he/she feels unable to replicate the success of those who have
accumulated a lot of housing wealth. However, an increase in housing inequality
among a much more precise reference group, defined as those of the same age,
education and gender living in the same city, provides a strong signalling effect. If
others with very similar characteristics have been able to build housing wealth, it
provides hope that he/she can as well. These results are consistent with the prediction
74
of the conceptual model in Section 3.2. The signalling effect is likely to dominate in
an unstable environment in which there are opportunities for upward social mobility,
if one feels that those who are successful can be emulated, creating anticipatory
feelings.
Another reason for the positive effect of within-group inequality on happiness is that
individuals have different tastes for within-group and between-group inequality,
perceiving the former as equal and the latter as unequal (Ferrer-i-Cabonell & Ramos,
2014). Models of relative concern suggest that some individuals have compassion and
concern for those who own less than them, while others have pride and gain
satisfaction from others having less. The presence of compassion seems to be the basis
of inequality aversion and presence of pride could generate a positive relationship
between inequality and happiness. Even in a rivalry model in which pride dominates,
a distinction can be made between endowment and reward inequality which have
negative and positive effects on happiness, respectively (Hopkins, 2008).
In models 5 and 6 we examine the non-linear relationship between housing wealth
inequality and happiness by adding the square terms of Gini coefficient or Theil index
in the specifications. The results in Model 6 show that the coefficient for the squared
term of the Theil index is significant and negative, suggesting that housing wealth
inequality and happiness exhibit an inverted U-shaped relationship. For an individual
with average housing wealth, the inflection point of the Theil-happiness relationship
is 0.81. The value of inflection point is relatively high, considering that the mean and
median values of the Theil index in the full sample are 0.35 and 0.33, respectively.
This finding is consistent with studies that have found a similar non-linear relationship
between income inequality and happiness (Yu & Wang, 2017).
One plausible explanation for this finding is that the inverted U-shaped relationship is
determined by the relative strength of the jealousy effect and signalling effect. Up to a
certain level of inequality, housing wealth of the region-gender-age-education
reference group might seem most attainable, and hence, an increase in inequality
signals an opportunity to obtain greater housing wealth in the future, which makes
individuals happier. However, as the level of inequality in housing wealth increases
beyond a critical point, the housing wealth of individuals at the top of the distribution
75
becomes out of reach for most members in the reference group. As a result, higher
inequality makes individuals less hopeful of realizing upward wealth mobility and
engenders a jealousy or status effect, which lowers happiness.
The results across Models 1-6 also show that own housing wealth has a significant and
positive effect on happiness, after controlling for other factors potentially correlated
with happiness. A standard deviation increase in housing wealth is associated with an
increased happiness score of approximately 0.03 points. This finding is consistent with
those of Otis (2017).
Table 3.3 presents the fixed effects results for housing wealth and housing wealth
inequality for different numbers of houses. The results suggest that housing wealth
associated with the first and second houses is positively related with one’s happiness.
Table 3.3
Fixed effects estimates
(1)
0.1363***
(3.64)
-0.0235
(-1.54)
0.0096
(0.63)
Gini – 1 house
st
Gini – 2nd house
Gini – 3rd house
Theil – 1st house
Theil – 2nd house
Theil – 3rd house
Wealth of 1st house
0.0072***
(4.77)
0.0064***
(3.26)
0.0065
(1.56)
38,299
0.0394
Wealth of 2nd house
Wealth of 3rd house
N
adj. R2
(2)
0.0769***
(3.20)
-0.0052
(-0.87)
0.0021
(0.46)
0.0073***
(4.79)
0.0061***
(3.15)
0.0067
(1.62)
38,299
0.0393
Notes: t statistics in parentheses; * p < 0.10, ** p < 0.05, *** p < 0.01; all specifications include a full set
of controls as specified in Appendix Table A1 as well as wave fixed effects; full results are available
from the authors.
76
This finding is consistent with previous studies that have found that the number of
houses one acquires matters for subjective wellbeing (Cheng et al., 2016). However,
only the housing wealth inequality of the first house has a significant and positive
relationship with happiness, while the inequality of the second and third houses has no
significant association with happiness. The effect size is slightly greater than that of
total housing wealth reported in models 3-4 in Table 3.2. Increasing the Gini
coefficient and Theil index of the first house by one standard deviation is associated
with an increase in an individual’s happiness by 0.023 points and 0.018 points,
respectively.
Table 3.4 presents the estimates of the CIs for happiness and housing wealth and
decomposition results for the contribution of housing wealth to wealth-related
happiness inequality. The wealth-related CIs for happiness are all positive, suggesting
that higher happiness is more concentrated among people with higher housing wealth.
The average total housing wealth-related CI for happiness is 0.0436 when the reference
group is defined as city of residence, gender, age and education. Of the three houses,
the housing wealth-related CI from the first house for happiness is the highest (0.0408),
slightly lower than that of total housing wealth-related happiness inequality. Housing
wealth-related CIs from the second and third houses are 0.0142 and 0.0029,
respectively. In contrast to the wealth-related CIs for happiness, the extent of total
housing wealth inequality is only 0.1178, which relatively lower than that of housing
wealth from the first and second houses. The CI for housing wealth from the second
house is the highest, reaching 0.3626, followed by the CIs for wealth from the first and
third house.
We next examine the contribution of housing wealth to happiness inequality. The
contribution of total housing wealth inequality to happiness inequality is estimated
based on the fixed effects estimates of Model 3 in Table 3.2, and the contributions of
wealth inequalities from different numbers of houses are estimated based on the
estimates of Model 1 in Table 3.3. The decomposition analysis shows that total
housing wealth contributes 6.49 per cent to happiness inequality. As expected, wealth
from the second house is the biggest contributor to happiness inequality, accounting
for 8.52 per cent. Meanwhile, the contributions of wealth from owning the first and
third house account for 6.41 and 1.64 per cent of the variation in happiness inequality.
77
Table 3.4
Decomposition of the concentration index of happiness
CI of happiness
CI of wealth
%
All houses
0.0436
0.1178
6.49
1st house
0.0408
0.1199
6.41
2nd house
0.0142
0.3626
8.52
3rd house
0.0029
0.0993
1.64
Notes: all specifications include a full set of controls as specified in Appendix Table A3.1 as well as
wave fixed effects.
3.6
Robustness checks
To check whether our results are biased by omitted variables, we adopt the approach
proposed by Oster (2019). Table 3.5 presents the results for this robustness check. The
first column presents the effects of housing wealth and its inequality, without any
control variables, and relevant robust standard errors and R-squared values. Column 2
presents the estimates with the full set of controls (adapted from Table 3.2). Column 3
shows the bias-adjusted treatment effects and standard errors under the assumption
that Rmax=1.3R (Rmax=0.0503) and δ=1. All three adjusted treatment effects for housing
wealth and inequality have the same sign as the estimated effects. The bias-adjusted
coefficients are still significant at the 5 per cent confidence level. The bounds of the
set [𝛽̃, 𝛽 ∗ (𝑅𝑚𝑎𝑥 , 1)] does not include zero and falls within +/−2.8 standard errors of
the controlled estimates. Although the inclusion of controls causes the coefficients on
housing wealth inequality to move away from zero, we find that including a full set of
controls and unobservables does not lead to significantly different conclusions than
just including the controls. The treatment effects suggest that a one standard deviation
increase in the Gini coefficient and Theil index lead to a 0.023-point and 0.020-point
increase in the happiness score, respectively, slightly higher than the effect sizes
estimated based on just including the controls. Moreover, there is only a small
movement in the coefficient on housing wealth toward zero when a full set of controls
is included, decreasing from 0.0099 to 0.0078. Column 4 calculates the values of δ
such that β=0 and Rmax=0.0503. The value of δ for housing wealth is greater than one,
while the values of δ for inequality are negative. This is because the inclusion of
controls has moved the coefficients away from zero instead of toward zero. However,
their absolute values exceed one. Both robustness checks suggest unobservables are
78
not biasing the estimates and that the coefficients estimated in the regression with
controls are robust.
Table 3.5
Robustness check: coefficient stability
Baseline effect 𝜷̇
(S.E.) [R2]
̃
Controlled effect 𝜷
Gini
0.0547 (0.0346) [0.0001]
0.1201 (0.0367) [0.0393]
0.1355 (0.0627)
-9.16
Theil
0.0176 (0.0221) [0.0000]
0.0668 (0.0230) [0.0392]
0.0797 (0.0393)
-5.77
Housing
wealth
0.0099 (0.0015) [0.0018]
0.0078 (0.0016) [0.0393]
0.0069 (0.0031)
7.66
(S.E.) [R2]
Bias-adjusted 𝜷∗
Rmax=1.3R
δ for β=0
given Rmax
In models 1-4 in Table 3.2 we provide separate results for the effects on happiness of
general provincial inequality (as a reference) and within-reference group inequality
(the focus of this paper). In a study on income inequality and happiness in urban China,
Jiang et al. (2012) control for both within-group and general inequality and suggest
that one should distinguish between income inequalities within different social groups
that are arguably more unfair than general inequality, which is relatively neutral. As a
robustness check, in models 1 and 2 in Table 3.6 we include both within group housing
wealth inequality and provincial general housing wealth inequality. The results are
consistent with those in models 1-4 in Table 3.2.14
Thus far, we have followed the standard practice by adding one to the amount of
housing wealth prior to the log transformation in order to accommodate households
with no urban housing wealth. We conduct further robustness tests to ensure that our
results are not biased by the log transformation approach or by samples that have zero
housing wealth.
14
We also tried alternative specifications in which we controlled for housing wealth inequality at the
province level, at the city level and within the city-gender-age-education defined reference group. The
results are reported in Appendix Table A3.3. When we control for all three simultaneously in the same
specification, housing wealth inequality defined at the city level and at the city-gender-age-education
level have a positive and significant effect on an individual’s happiness. The effect size of housing
wealth inequality at the city level is relatively higher. A one standard deviation increase in housing
wealth at the city level (a 0.08 increase) is associated with a 0.036 points increase in the happiness score.
79
Table 3.6
Robustness check: fixed effects estimates with different specifications
+ provincial inequality
(1)
Gini – within
group
(2)
0.1280
(3)
(4)
(5)
***
0.1245
(3.49)
Theil – within
group
***
***
(8)
***
-0.4689
(-3.19)
(-2.80)
***
Remove zero
wealth
housing wealth
wealth
samples
categories
(12)
(13)
(10)
(3.13)
0.1290
***
(3.25)
housing
0.1129***
(3.07)
***
(3.33)
***
-0.5096
(-3.05)
-0.3101***
(-3.91)
0.3679
***
(3.07)
0.0765
-0.2873
***
0.1129
(3.60)
***
-0.3186
(11)
***
***
***
-0.5317
- housing
zero housing wealth
0.1320
0.0716
(2.95)
+ provincial inequality &
(9)
***
(3.50)
0.0678
(-4.35)
Zero housing
wealth (ref: nonzero housing
wealth)
Housing wealth
0.1283
(3.39)
0.0759
Theil – province
(7)
(6)
***
(3.30)
Gini – province
IHS transformation
+ zero housing wealth
0.3665
***
(4.03)
(4.01)
0.0077***
0.0078***
0.0348***
0.0346***
(4.92)
(4.92)
(4.90)
(4.87)
(-4.23)
0.3845
***
0.3786
***
0.3686***
-0.0772***
(4.12)
(4.03)
(-3.84)
0.0362***
0.0357***
(5.09)
(5.02)
0.3761
(4.22)
(4.15)
0.0370***
0.0366***
0.0277***
0.0278***
(5.21)
(5.16)
(6.68)
(6.68)
***
0.0406***
(5.15)
Housing wealth
(ref: zero housing
wealth)
Low
0.0443**
(2.06)
0.0829***
Medium
(3.95)
0.1133***
High
(5.07)
N
adj. R2
38,299
38,299
0.0392
*
38,299
0.0394
Notes: t statistics in parentheses; p < 0.10,
available from the authors
**
p < 0.05,
0.0394
***
38,299
0.0397
38,299
0.0396
38,299
0.0394
38,299
0.0390
38,299
0.0389
38,299
0.0400
38,299
0.0402
38,299
0.0383
34,036
0.0430
p < 0.01; all specifications control for a full set of controls as specified in Appendix Table A3.1 as well as wave fixed effects; full results are
80
38,299
0.0391
In models 3-6 in Table 3.6, we re-estimate models 1-4 in Table 3.2, adding a dummy
variable set equal to 1 if the respondent has no housing wealth in addition to controlling
for housing wealth. The results are consistent with those reported in models 1-4 in
Table 3.2. That the dummy variable for zero housing wealth is positive and significant
suggests that households who have no housing wealth are happier than those with
housing wealth, once we control for the positive effect of housing wealth on happiness.
As an alternative to taking the log transformation of the wealth measures, in Models
7-8 we apply the inverse hyperbolic sine (IHS) transformation to measures of housing
wealth, debt, assets and household income (Friedline et al., 2015) and re-estimate
model 3 in Table 3.2.15 The results for the within-group Gini, with the IHS transformed
wealth measure and the log transformed wealth measure are consistent.
In models 9 and 10 in Table 3.6, we re-estimate models 1 and 2 in Table 3.6, adding a
dummy variable set equal to 1 if the respondent has no housing wealth in addition to
controlling for housing wealth. As in models 3-6, the dummy variable for households
with zero housing wealth is positive. The results in models 9 and 10 suggest that first
two columns in Table 3.6 are robust to this alternative approach to dealing with
households with no housing wealth. In model 11 we do not control for housing wealth
and find that the coefficient on the dummy for zero housing wealth is negative and
significant, consistent with our interpretation for the coefficient on the dummy variable
for households with zero housing wealth in models 3-6 and 9-10. In model 12 we
restrict the sample to those who have housing wealth and remove those who do not.
The approach proposed by Semykina and Wooldridge (2013) is employed to address
possible sample selection bias in estimation. In model 13 we replace the continuous
housing wealth variable with a categorical variable. In models 11-13 the findings for
the within-group Gini are consistent with the main results.
Since housing wealth inequality is correlated with non-housing wealth inequality and
household income inequality within the city-gender-age-education defined reference
group (the pairwise correlation coefficient between two of these three Gini coefficients
ranges from 0.54 to 0.62.), as a further check we test whether our results are driven by
the non-housing wealth inequality and household income inequality. Appendix Table
15
The IHS transformations can be expressed as 𝑖ℎ𝑠(𝑥) = log(√𝑥 2 + 1 + 𝑥).
81
A3.4 shows that our point estimate on the impact of housing wealth inequality is still
significant and not affected by the inclusion of non-housing wealth and household
income inequalities. This result suggests that the effect of housing wealth inequality
on an individual’s happiness is distinct from non-housing wealth inequality and
household income inequality.
3.7
Conclusion
Housing wealth inequality in urban China has been increasing in recent years. This is
important because inequality in housing wealth is a major contributor to total wealth
inequality in urban China. It is also an extremely visible indicator of differences
between the ‘haves’ and ‘have nots’ and, as such, likely to be important when it comes
to relative effects. In this respect, although China has only recently developed a
housing market, it is illustrative of concerns about the effects of rising house wealth
inequality in other countries (Piketty, 2014). While a number of studies have examined
the effect of inequality in consumption, income and overall household wealth on
happiness, there has, to this point, been no in-depth treatment of how housing wealth
and inequality in housing wealth is associated with happiness, either for China or other
countries. This is in spite of calls for more attention to be given internationally to the
role of housing wealth inequality (Arundel, 2017).
The picture that emerges from our study is that housing wealth is positively associated
with happiness in urban China. This is true for the in-group comparison and when city
is the reference point. This is consistent with extant findings from studies such as Otis
(2017) and Wang et al. (2018). There are, however, diminishing returns, to wealth
from owning a second house and the wealth from owning a third house is statistically
insignificant.
A general increase in housing wealth inequality at the province level lowers happiness.
The reason is that individuals are unable to relate to those at the top end of the
distribution and, hence feel unable to replicate their success. This engenders a jealousy
effect. However, an increase in housing wealth inequality within a narrowly defined
reference group – those of the same gender and similar age and education living in the
same city – up to a certain point increases happiness. The reason is that individuals
feel empowered by the success of others with very similar characteristics to them and
82
this generates a signalling effect in which people feel that success for them is just
around the corner. If others of the same age, education and gender, living in the same
city as me have been able to accumulate housing wealth, I should be well placed to
replicate their success. The signalling effect dissipates when housing wealth inequality
passes a threshold at a relatively high level of inequality. Beyond the threshold, the
success of those at the top of the distribution appears out of reach, even when, on paper,
they seem similar to me. I have ‘missed the boat’ - increase in housing wealth
inequality makes me jealous of what they have achieved and serves to lower my
happiness.
An important policy implication of our findings is that the government should take
steps to reduce general inequality in housing wealth at the provincial level, which
lowers happiness. One step that the Chinese government is taking is to subsidise lowincome housing. For example, in 2017, the government planned to build two million
units of public rental housing to provide affordable homes for low-income groups
(Than, 2017). However, as Huang (2013) discusses, there have been reports of local
governments relabelling existing housing as new affordable housing, while, in other
cases, the new housing is being built in remote locations with poor services. And the
better-quality housing that is being built in good locations is often ending up in the
hands of middle-income households, ministries or other government agencies who
often acquire multiple houses. Some cities, such as Chongqing and Shanghai, have
introduced fixed asset taxes to curb housing wealth at the top of the distribution, but
the taxes have had limited effect. While an argument in favour of a fixed asset tax our
finding of diminishing returns to housing wealth from owning a second and third
house, politically, few in the Chinese government want a more general fixed asset tax
because they are among those who have the most housing wealth and would lose most
from such a tax (Murayama, 2016). An alternative policy option is to create more
opportunities for those without housing wealth to build at least modest levels of
housing wealth. If individuals can see realistic opportunities to build wealth from the
growth in housing prices and can see that others with characteristics similar to them,
living in the same city, have been successful in so doing, housing wealth inequality up
to relatively high levels can provide a strong signalling effect.
83
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89
APPENDICES
Table A3.1
Summary statistics, China Household Finance Survey 2011, 2013
and 2015
Variable
Definition
Housing wealth Household housing wealth (of all
houses) in logarithm (inverse
hyperbolic sine (HIS) transformation)
Debt
Household debt, in logarithm
Assets
Income
Household assets excluding housing
wealth, in logarithm
Household income, in logarithm
Male
Male=1; female=0
Age
Years
Standard
Deviation
4.22
2.78
4.78
11.08
1.89
10.18
2.77
48.21%
Age squared
Education
Mean /
percentage
11.41
Years
51.45
14.99
2,871.39
1,585.36
10.26
4.14
Marital status:
Unmarried
Reference group
5.10%
Married
84.25%
Other
10.65%
Risk aversion
Scale: high=1; low=5
4.02
1.20
Health status
Scale: very healthy=1; very
unhealthy=5
Yes=1; no=0
2.88
1.08
Medical
insurance
Superannuation Yes=1; no=0
91.44%
80.85%
Job status
Employed
Reference group
27.91%
Self-employed
10.24%
Agricultural
work
Other jobs
8.19%
5.60%
No work
48.06%
Family size
Number of family members
2.61
1.58
Children
Number of children
0.82
1.25
Province
Details available from authors
90
Table A3.2
Decomposition of Gini coefficient by source of housing wealth (full
sample)
Housing wealth source
Wealth
share
(Sk)
Gini
coefficinent
(Gk)
Wealth of 1st house
Wealth of 2nd house
Wealth of 3rd house
Total housing wealth (G)
0.8026
0.1474
0.0253
0.6154
0.9309
0.9899
0.6377
Gini
Relative
correlation contribution
(Rk)
[(Sk × Gk × Rk)
/G]
0.9668
0.7488
0.8523
0.1833
0.9139
0.0358
Notes: Sk measures how imporant the wealth source is with repsect to total wealth; Gk measures how
equally or unequally distributed the wealth source is; Rk measures how the wealth sources and the
distribution of total wealth are correlcted; relative contribution measures the share of individual wealth
source in total housing wealth inequality.
91
Table A3.3
Fixed effects estimates of housing wealth inequality within
different reference groups on happiness
(1)
Gini – province
(2)
(3)
-0.4917***
-0.7567***
(-2.94)
Gini – city
(4)
(-4.40)
0.3714***
0.4520***
(3.90)
(4.44)
Gini – group
0.1201***
0.0939**
(3.27)
(2.48)
0.0069***
0.0074***
0.0078***
0.0078***
(4.47)
(4.76)
(5.00)
(4.97)
N
38,299
38,299
38,299
38,299
adj. R2
0.0386
0.0389
0.0387
0.0400
Housing wealth
Notes: t statistics in parentheses; * p < 0.10, ** p < 0.05, *** p < 0.01; all specifications control for a full
set of controls as specified in Appendix Table A3.1 as well as wave fixed effects; full results are
available from the authors.
92
Table A3.4
Housing wealth, non-housing wealth and happiness
Happiness
0.1239***
(3.01)
-0.0223
(-0.62)
0.0518
(1.33)
0.0076***
(4.87)
-0.0027**
(-2.27)
0.0307***
(7.32)
0.0045
(1.43)
37,969
0.0387
Gini – housing wealth
Gini – non-housing wealth
Gini – household income
Housing wealth
Debt
Assets
Income
N
adj. R2
Notes: t statistics in parentheses; * p < 0.10, ** p < 0.05, *** p < 0.01; all specifications control for a full
set of controls as specified in Appendix Table A3.1 as well as wave fixed effects; results are available
from the authors.
93
CHAPTER 4
PETROL PRICES AND
SUBJECTIVE WELLBEING
This chapter presents co-authored work with Russell Smyth and Sefa Awaworyi
Churchill. This paper uses unit record data from the Household, Income and Labour
Dynamics in Australia (HILDA) Survey. The Household, Income and Labour
Dynamics in Australia (HILDA) Survey was initiated and funded by the Australian
Government Department of Social Services (DSS) and is managed by the
Melbourne Institute of Applied Economic and Social Research (Melbourne
Institute). The findings and views reported in this paper, however, are those of the
authors and should not be attributed to either DSS or the Melbourne Institute. We
thank David Gargett from the Department of Infrastructure, Regional Development
and Cities for sharing the city-level monthly diesel and unleaded petrol price data. An
earlier version of this paper was presented at a PhD conference in the Faculty of
Business and Economics at Monash University. We thank conference participants,
Choon Wang, Mark Wooden, Kenneth Clements and two anonymous referees for very
helpful comments on earlier versions of this paper.
94
Abstract
We examine the effect of petrol prices on subjective wellbeing (SWB) using household
panel data. To do so, we use 17 waves of the Household, Income and Labour Dynamics
in Australia (HILDA) survey. Based on our preferred instrumental variable estimates,
we find that a standard deviation increase in petrol prices leads to a decline of 0.0157–
0.0245 standard deviations in SWB. The finding that increases in petrol prices
significantly lower SWB is robust to alternative measures of wellbeing and alternative
ways of addressing endogeneity, as well as employing different sources of fuel price
data measured at a range of frequencies. We also examine the channels through which
petrol prices influence SWB and find that maintaining social networks is an important
way through which petrol prices influence SWB.
Keywords: subjective wellbeing; life satisfaction, petrol prices, Australia
95
4.1
Introduction
There is a growing interest among policymakers in using measures of subjective
wellbeing (SWB) to evaluate the impact of policy (see eg. DiMaria, Peroni &
Sarrccino, 2019; Sachs, Becchetti & Annet, 2016). Improving SWB has, thus, become
an important policy objective in many countries. This development reflects greater
attention, among economists, to indicators of social progress other than Gross
Domestic Product (GDP) more generally. The Stiglitz Commission (Stiglitz, Sen &
Fitoussi, 2009), for instance, recommended the use of subjective measures, such as
SWB, to measure, and monitor, social progress. Economists are, thus, increasingly
turning their attention to understanding what determines how satisfied people are with
their lives and why some people are more satisfied with their lives than others (see for
e.g. Awaworyi Churchill, Appau & Farrell, 2019; Barring-Leigh & Escande, 2018;
Cheng, Mishra, Nielsen, Smyth & Wang, 2017; Dolan, Peasgood & White, 2008).
Running parallel with increased interest in SWB, spurred by the adverse effects of the
first oil price shock on consumers, economists have spent a lot of time better
understanding the implications of movements in petrol prices. For example, the
feathers and rockets hypothesis, which states that when the price of oil increases, retail
petrol prices shoot up like rockets, but when the opposite occurs, they float down like
feathers (Bacon, 1991) has been the subject of several studies (see for e.g. Bachmeier
& Griffin, 2003; Borenstein, Cameron & Gilbert, 1997; Chen, Finney & Lai, 2005;
Duffy-Deno, 1996; Galeotti, Lanza & Manera, 2003; Honarvar, 2009; Liu, Margaritis,
& Tourani-Rad, 2010; Valadkhani, 2013a). Other studies have sought to better
understand pricing dynamics in petrol markets (see for e.g. Chua, De Silva, & Suardi,
2017; Davey, 2010; Valadkhani, 2013a, 2013b; Wang, 2008, 2009). An implicit
motivation for such studies is that petrol price increases, as well as volatility in petrol
prices, have adverse welfare effects on consumers and that through improving our
understanding of petrol price movements we can reduce harmful welfare effects.
A natural extension of such studies, particularly given economists’ keen interest in the
antecedents of SWB at the individual level, is to directly examine how petrol price
movements affect SWB, controlling for the myriad other factors correlated with SWB.
Such an approach provides an estimate of the magnitude of the effect of changes in
petrol prices on SWB. Further, by calculating the income equivalence of the change in
96
SWB due to a change in petrol prices, it can be used to measure the economic
significance of a change in petrol prices. Such an estimate can be very useful in
evaluating the impacts of policies related to setting petrol prices, which complement
findings from studies of petrol price dynamics.
We examine the relationship between petrol prices and SWB employing household
panel data. Specifically, we use 17 waves of longitudinal data from the Household,
Income and Labour Dynamics in Australia (HILDA) survey, covering the period 20012017. We know the exact month in which each participant was interviewed in the
HILDA survey, so for each wave we are able to match monthly city-level petrol price
data for the city in which the participant lives in the month in which the participant
was interviewed to the participant’s responses to the life satisfaction question: “How
satisfied are you with your life?” In addition to controlling for observed characteristics
of participants that are correlated with SWB, the use of household panel data allows
us to account for unobserved factors that eliminate the influence of unobserved timeinvariant individual fixed effects. We also pay careful attention to addressing the
endogeneity of petrol prices using both external and internal instruments.
Our main identification strategy is to instrument for petrol prices using a priceweighted index of leading companies involved in the exploration, development and
production of oil listed on the New York Stock Exchange (NYSE) - the NYSE Arca
Oil Stock prices index. We match the NYSE Arca Oil Stock price in the month in
which the participant was interviewed with the petrol price in the city in which the
participant lived in that month. Adopting this approach, our two-stage least squares
(2SLS) estimates suggest that a standard deviation increase in petrol prices are
associated with a decline in SWB between 0.0157 and 0.0245 standard deviations. This
result is robust to alternative ways of addressing endogeneity, the use of both unleaded
and diesel petrol prices from different sources and at different frequencies and various
sensitivity checks, including use of alternative specifications. We also find that
maintaining social networks - maintaining contact with family and friends outside the
home - is an important channel through which petrol prices have an adverse effect on
SWB.
97
Rising petrol prices have been a cause of concern to consumers in many countries in
the world. For example, in the UK, consumers have sporadically protested against
petrol price rises over the last two decades; most notably in the 2012 fuel crisis. In
2018 Gallup polling in the US, 35 per cent of respondents reported that gasoline price
rises caused them financial hardship and 41 per cent said that the high price of gasoline
would cause them to drive less (Norman, 2018). Most recently, in 2019 petrol price
rises sparked widespread protest in France.
Petrol price increases in Australia are highly representative of what has happened in
many developed countries that are heavily reliant on imported petroleum
(Commonwealth of Australia, 2019). Since 2000, the annual national average price of
petrol in Australia has increased more than 50 per cent from $0.89 per litre to $1.47
per litre at the end of 2018. Frustration at rising petrol prices have routinely generated
spontaneous protests among motorists. For example, on the back of a social media
campaign, an estimated 160,000 motorists participated in a two-day “National Fuel
Strike” in October 2018 (Drew, 2018).
Our contribution is related to at least three strands of literature that are broadly
concerned with the effect of petrol price movements on wellbeing. One set of studies
examine the effect of changes in petrol prices on participation in physical activity and
health outcomes. Studies have found that increases in petrol prices lead to
improvement in air quality (Shaw, Hales, Edwards, Howden-Chapman & Stanley,
2018), a reduction in obesity rates (Coutemanche, 2011) and increases in individual
physical activity (see for e.g. Hou et al., 2011; Sen, 2012). These studies show that
higher petrol prices reduce car air pollutants in the environment; encourage individuals
to use other modes of transport, such as walking, bicycling or taking public transport;
increase the amount of time spent at home doing yard work; and reduce the frequency
of eating out at restaurants, each of which tend to promote healthy lives. Leading a
healthy life has been shown to be correlated with higher SWB (Dolan et al., 2008).
We differ from these studies in that they do not specifically examine the effect of petrol
prices on SWB.
A second set of studies to which our contribution is related is the literature that links
leisure activities with SWB (see for e.g. Kuykendall, Tay & Ng, 2015; Liu & Yu, 2015;
98
Reynolds & Lim, 2007; Sirgy, Uysal & Kruger, 2017). These studies proffer that
satisfaction with leisure activities favourably contribute to SWB. In particular, time
spent driving for a weekend family getaway or sight-seeing has a positive effect on
life satisfaction (Morris, 2015). Driving can also be important to maintain social
networks that are important for a happy life. Harrison and Ragland (2003) find that
giving up, or reduced, driving has adverse consequences, including increased
dependence on others for transport, loss of independence, reduced out-of-home
activity, increased depressive symptoms and decreased life satisfaction. An important
intermediate input to making people happier via travel is the cost of transportation
(Stanley & Vella-Brodrick, 2009), with higher petrol prices making it more expensive
to commute, curtailing leisure activities outside the home and reducing opportunities
for social networking.
The studies closest to ours, however, are Graham and Chattopadhyay (2010) and
Boyd-Swan and Herbst (2012) who each examine the relationship between gasoline
price and an individual’s self-reported life satisfaction in the US. Graham and
Chattopadhyay (2010) use a cross-sectional Gallup Daily poll survey for the United
States, merged with daily national average gasoline prices over the period January
2008 to December 2009. These authors find a negative correlation between gasoline
prices and individual wellbeing. Boyd-Swan and Herbst (2012) model the relationship
between state-level gasoline price and individual SWB using a repeated crosssectional survey for the US over the period 1985—2012, similarly finding a negative
relationship between gasoline prices and SWB.
We differ from these studies in several important ways. The first is that we provide
some firm evidence on the relationship between petrol prices and SWB for a country
other than the US which has experienced rising petrol prices that one would expect to
affect SWB. Second, beyond our focus on a country other than the US, we differ
methodologically from these studies. While Graham and Chattopadhyay (2010) and
Boyd-Swan and Herbst (2012) used cross-sectional data and do not address the
endogeneity of petrol prices, we use panel data and employ a range of approaches to
address endogeneity. Specifically, using panel data allows us to control for time
invariant unobserved individual specific characteristics that may simultaneously affect
petrol price and SWB, but were not accounted for in these two studies.
99
Importantly, petrol prices in Australia exhibit high volatility, consistent with a rocket
and feather effect (Valadkhani, 2013a; Valadkhani & Smyth, 2018). Between the last
quarter of 2018 and the first quarter of 2019 alone, monthly city-level average petrol
prices fluctuated between a low of $1.17 per litre and a high of $1.65 per litre,
reflecting the highly volatile nature of petrol prices in Australia.16 The large variation
in petrol prices that has occurred in Australia makes it a particularly useful setting in
which to draw causal inferences.
A third difference is that Graham and Chattopadhyay (2010) and Boyd-Swan and
Herbst (2012) use average state-level petrol price to proxy petrol prices faced by
individuals. Average state-level petrol prices, however, might not accurately reflect
the actual petrol prices in the individual’s local geographic area at the time that they
reported their life satisfaction. We address this issue by taking advantage of knowing
the month and the city in which the participant was interviewed. Specifically, we
match the petrol price in the city in which the person lives in the month in which they
were interviewed, in order to capture the relationship between petrol prices facing the
participant and their self-reported SWB more precisely.
Fourth, unlike these earlier studies, we examine several channels through which petrol
prices potentially influence a person’s SWB. Specifically, we consider the mediating
role of maintaining social networks out of the home - seeing extended family and
keeping in touch with friends - and consumption choices, proxied by eating out of
home.
The rest of this paper is structured as follows: Section 4.2 provides a brief discussion
of the underlying mechanisms that links petrol prices to SWB. Section 4.3 describes
the data and variables used in this study, while Section 4.4 sets out the empirical
strategy adopted in this study. The discussion of the results is contained in Section 4.5.
The final section concludes.
16
Monthly city-level petrol price data was provided by David Gargett, Department of Infrastructure,
Regional Development and Cities, in personal communication, 2019.
100
4.2
Why should petrol prices influence subjective wellbeing?
Boyd-Swan and Herbst (2012) present a simple model in which utility is expressed as
a function of consumption of goods and services, current health, leisure and a set of
demographic factors. In this model, consumption can either be health enhancing, for
example, through participating in physical activity or eating healthy foods, or health
reducing through, for example, eating unhealthy calorie dense foods or engaging in
sedentary activities.
The model also captures the benefits of leisure travel activities. Past research has
linked leisure activities with SWB (see for e.g. Inoguchi, 2018; Liu & Yu, 2015;
Newman, Tay & Diener, 2014; Sirgy et al., 2017). Sirgy et al. (2017) argues that every
leisure activity is associated with certain goal-benefits related to basic needs (health,
safety, sensation-seeking, economic, hedonic and escape) as well as growth needs
(symbolic, aesthetic, mastery, moral, relatedness and distinctiveness benefits). The
central idea is that the more that leisure activities bring benefits associated with basic
and growth needs, the greater the likelihood that such activities will contribute
significantly to satisfaction with leisure activities, ultimately, enhancing SWB.
Within this framework, an increase in petrol prices are predicted to have ambiguous
effects on SWB that operate through two main channels. First, price-induced effects
to leisure activities and consumption generate substitution and income effects that
could lead to behavioural change that influence health and SWB. Second, the
economic environment could directly affect SWB without corresponding changes in
individual behaviour.
4.2.1
Substitution effects
When petrol prices rise, the opportunity cost of undertaking leisure activities involving
driving increases. This results in substitution effects because, as the price of petrol
rises, the relative cost of engaging in non-driving alternatives decrease which
encourages a shift to these activities. Boyd-Swan and Herbst (2012) argue that people
respond to rising petrol prices by driving less which, in turn, adversely affects SWB
by reducing engagement in wellbeing-enhancing leisure activities, associated with
basic and growth needs (Sirgy et al., 2017), which includes maintaining, and building,
social networks outside the home.
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For many people, the main reason for driving the car through the week is the daily
commute to work. This is particularly the case in countries such as Australia in which
a high proportion of the population live in the outer suburbs of the large cities, where
housing is relatively less expensive, and undertake long commutes into the city to work
each day (Awaworyi Churchill & Smyth, 2019). An increase in petrol prices will
reduce the relative cost of taking public transport to work. However, in the Australian
case, at least, the outer suburbs are not well serviced by public transport and, in peak
commuting times, buses and trains are crowded making it very difficult to get a seat.
There is also a general lack of public transport infrastructure serving the outer suburbs
in most of the major Australian cities. As Armstrong, Davison, Malan, Gleeson and
Godfrey (2015, p.21) state: “Fringe developments are characterised by low housing
and low employment density, limited (if any) mixed-use development and poor access
to public transport. Together, this increases distances between where people live and
where they need to travel for work, shopping, socialising and recreating”. Thus, taking
public transport invariably involves a much longer and less comfortable commute,
which adversely effects SWB (see for e.g. Lorenz, 2018; Zhu, Li, Chen, Liu & Zeng,
2019).
An increase in petrol prices could generate substitution effects which enhance SWB.
Studies have found that as petrol prices rise, some individuals substitute away from
driving in favour of more physically demanding modes of transportation that may
include walking or cycling, which are correlated with having better health and higher
SWB (see for e.g. Jones, Steinbach, Roberts, Goodman & Green, 2012; Ma, Zhang,
Ding & Wang, 2018). Individuals may respond to rising petrol prices by reducing
consumption of calorie-dense foods at restaurants and increase their consumption of
healthier home-cooked food. These substitution effects are associated with positive
outcomes in terms of realizing basic and growth needs as well as having favourable
health effects which contribute to higher SWB.
4.2.2.
Income effects
Rising petrol prices might also induce income effects that can reduce SWB. This is
likely to be the case when few welfare-enhancing alternatives are available. In the
Australian case, poor public transport options mean that many people have no other
102
option but to absorb the cost of higher petrol prices (Currie, Delbosc & Pavkova,
2018). In these circumstances, it is likely that individuals will allocate more disposable
income to fuel expenses, which means that less income will be available for other
wellbeing-enhancing activities. For instance, individuals
may forgo
gym
memberships, decrease frequency of health check-ups and decrease the frequency of
going to movies with the family, all of which adversely impact on SWB.
4.2.3.
Macro-economic conditions and psychological health
Another conceptual argument stems from the work of Catalano and Dooley (1983), in
which they propose the economic stress hypothesis and find strong links between
macroeconomic conditions and psychological health. The economic stress hypothesis
states that rising fuel prices may increase anxiety and signal possible macroeconomic
uncertainty in the overall economy. Given that petrol prices are typically displayed on
large signs at the front of petrol stations, they are highly visible. Their visibility is
reinforced by the readily available apps that track petrol prices and indicate the petrol
stations offering the lowest prices. The economic stress hypothesis posits that people
make predictions about the state of the economy based on the movements in petrol
prices that they observe and draw inferences about implications for their lives. If petrol
prices increase people may perceive that this is a signal that the economy is not faring
well with adverse implications – for example higher taxes – which lower SWB.
4.3
Data and Variables
We use restricted release version 17 of HILDA survey and make use of data from wave
1 through to wave 17, covering the period 2001 to 2017. The HILDA survey is funded
by the Australian government’s Department of Social Services to collect nationally
representative longitudinal data, in order to facilitate research on economic and social
issues facing Australian households. An important feature of this survey is that the
same households and individuals are interviewed in repeat years, which allows us to
see how their lives are changing overtime. Along with the Panel Study of Income
Dynamics, British Household Panel Survey and German Socioeconomic Panel, it
represents one of the longest running household panels in the world.
The initial HILDA sample consisted of approximately 7,500 households and 19,900
individuals. In wave 11 an additional 5,462 individuals and 2,153 households were
103
added to account for the changes in the composition of the original households
(Summerfield et al., 2018). The HILDA survey interviews individuals aged 15 and
above, but we restrict our sample to only those who are at least 18 years old. One of
the main channels through which petrol prices potentially affect SWB is through an
individual’s ability to drive a vehicle. The minimum driving age varies between states
and territories in Australia. In most states it is 17 years old, while it is 16.5 years in the
Northern Territory and 18 years in Victoria. Hence, restricting the sample to those
aged 18 years and above, ensures comparability and consistency across all states and
territories. We match monthly city-level petrol price data to the month in which each
participant was interviewed in each survey year. Allowing for missing observations in
our main outcome and explanatory variables, our final sample consists of 14,953
individuals with 118,342 observations who are included in at least two waves of the
HILDA survey.17
4.3.1
Main outcome variable
Our main outcome variable, SWB, is a measure of overall life satisfaction based on
the HILDA survey question “How satisfied are you with your life?” Respondents were
asked to self-report scores to this question on a scale of 0—10, where 0 is labelled as
‘totally dissatisfied’ and 10 is ‘totally satisfied’. Other household panel surveys, such
as the British Household Panel Survey, the European Union Statistics on Income and
Living Conditions and the German Socioeconomic Panel ask this question in almost
the same form and it is widely used as a measure of SWB in the economics literature
(see for e.g. Grover & Helliwell, 2019; Headey & Yong, 2019; Solé-Auró & Lozano,
2019). Self-reported life satisfaction scores have been shown to be correlated with
other measures of wellbeing, such as daily mood ratings, recall of number of positive
and negative events and physiological measures of wellbeing, including the number of
‘genuine’ – Duchenne - smiles (Diener & Suh, 1997). Cummins (2018) demonstrates
that self-reported life satisfaction scores are reliable and stable over time.
17
There are 171,746 observations at the city-level containing data on life satisfaction and petrol prices.
When we cap age at 18, this number falls to 130,282 observations (i.e. we lose 41,464 observations).
When we restrict the sample to individuals appearing in at least two waves of the survey, the sample
falls to 126,520 observations (i.e. we lose 3,762 observations). We lose a further 8,178 observations,
giving us our final sample size of 118,342, due to missing variables for one or more of the control
variables.
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In our sample, the average score for life satisfaction is 7.83 out of 10 with a standard
deviation of 1.47 (see Table A4.1). Figure 4.1 plots the trend in the mean of the life
satisfaction scores of participants in our sample over time. The trends in our life
satisfaction scores are consistent with observed life satisfaction in western countries
(International Wellbeing Group, 2013). In Australia, Kubiszewski, Zakariyya and
Costanza (2018) and Nguyen, Fleming and Su (2015) find life satisfaction scores to be
stable and between the narrow ranges of 7.0 to 8.0.
Trends in life satisfaction in sample over time: HILDA waves 1-17
8
7.9
7.8
7.5
7.6
7.7
Life satisfaction scores
8.1
8.2
Figure 4.1
2001
2003
2005
2007
2009
Year
2011
2013
2015
2017
Source: Derived from HILDA
In Table 4.1, a simple breakdown of our data suggests that individuals who own a
vehicle have higher SWB than those who do not. Females and those who are married,
but do not have children, report higher life satisfaction scores than their counterparts.
Further disaggregation of the data at the subsample level shows that senior citizens,
aged 65 years and above, are more satisfied with their life than those in other age
categories. We also note that individuals who earn more than the median income are
happier with their life than those who are below the median level of income. However,
differences in education attainment and employment status do not appear to be
associated with differences in the life satisfaction scores of participants.
105
Table 4.1
Subjective wellbeing by various categories
Categories
Full sample
Vehicle ownership
Own a vehicle
Do not own a vehicle
Gender
Males
Females
Age groups
Ages 18—34
Ages 35—64
Ages 65+
Education level
High school and below
Tertiary education
Employment status
Employed
Unemployed
Household Income level
Less than median
More than median
Marital Status
Married
Not married
Children in household
Yes
No
Mean
7.83
Sample size
118,342
7.86
7.75
85,546
32,796
7.79
7.86
55,417
62,925
7.84
7.70
8.21
39,589
59,683
19,070
7.84
7.82
49,000
69,342
7.84
7.80
79,415
38,927
7.70
7.95
56,981
61,361
7.99
7.66
59,429
58,913
7.77
7.85
35,960
82,378
Notes: Subjective wellbeing is measured by life satisfaction on a scale of 0-10 (lowest = 0, highest =10)
As a robustness check on our main findings, instead of using responses to the life
satisfaction question, we use the Mental Health Inventory (MHI-5) scale and the
Kessler Psychological Distress Scale (K10), the latter of which is just contained in
waves 7, 9, 11, 13, 15 and 17 of the HILDA survey. Both seem particularly apt
measures given that the economic stress hypothesis states that rising petrol prices will
reduce individual’s psychological health via their perceived effect on macroeconomic
conditions (Catalano & Dooley, 1983). The MHI-5 and K10 are mental health scale
based on questions that reflect one’s nervousness, psychological fatigue, agitation and
depression. The five-item MHI-5 is measured on a 0—100 scale. The 10-item K10
106
questionnaire has a five-level response scale, which is aggregated to generate a mental
health scale with a minimum possible score of 10 (good mental health) and a maximum
possible score of 50 (poor mental health) (ABS, 2019a). We also employ a measure
of participants’ risk categories based on the K10 scale. In the latter, participants are
categorised as low risk of psychological distress if their K10 scores are within the
range 10—15, moderate risk if between the range 16—21, high risk if between the
range 22—29, and very high risk if between the range 30—50. This measure is
reported on a 1—4 ordinal scale, in which 1 corresponds with ‘low risk’ and 4
corresponds with ‘very high risk’. Descriptive statistics for the MHI-5 scale and both
versions of the K10 are contained in Table A4.1.
4.3.2
Petrol prices
Australia has a population of approximately 25 million people and 19.5 million
registered motor vehicles; of which, three quarters are powered by petrol and the other
quarter by diesel (Australia Bureau of Statistics, 2019). At the beginning of the
millennium, petrol prices averaged $0.78 per litre, but by 2018 the national average
price of unleaded petrol had increased to $1.47 per litre. The areas most affected by
higher petrol prices have been in regional Australia, in which petrol prices were
regularly higher than $1.60 per litre in 2018.
In our main results, we use city-level monthly unleaded petrol price data, which is
sourced from the Department of Infrastructure, Regional Development and Cities.18 In
sensitivity checks, we also employ a range of other petrol price data. First, we use city–
level monthly diesel prices over the same period, which are from the same source.
Second, we use annual diesel and unleaded petrol price data obtained at the city–level
from the Australian Institute of Petroleum website for the period 2004-2017.19 Third,
in order to incorporate analysis at a wider geographical area, we also obtain annual
data at the state–level from the Australian Institute of Petroleum website for both petrol
and diesel over the period 2002-2017 and 2004-2017, respectively. Fourth, we use
18
The data were provided by David Gargett, Department of Infrastructure, Regional Development and
Cities, in personal communication, 2019.
19
This data is publicly available at https://www.aip.com.au/
107
petrol and diesel price data sourced from Western Australia’s Fuel Watch website for
Western Australian regions for the period 2001-2017.20
4.3.3
Covariates
Individual SWB is correlated with a number of socio-demographic factors (see for e.g.
Ambrey & Fleming, 2014; Boyd-Swan & Herbst 2012; Dolan, Peasgood & White,
2008) for which we need to control. Consistent with the life satisfaction literature, we
control for variables such as age, gender, marital status, employment status, income
and education status, among others. Following Boyd-Swan and Herbst (2012), we also
control for state-level population density and per capita income in order to account for
state-level differences which might exist due to the degree of urbanization and wealth.
Boyd-Swan and Herbst (2012) argue that including population density and state–level
per capita income helps avoid finding a spurious relationship, due to changing trends
in population and economic conditions that can influence state transportation systems,
causing changes in demand and price of petrol.
4.3.4
Channels
We examine the role of social networks outside the home and consumption choices as
channels through which petrol price movements potentially effect SWB using
questions in specific waves. In waves 6, 10 and 14 of the HILDA survey, respondents
were asked a series of questions about their level of community participation or social
networks outside of their homes. Specifically, respondents were asked: “In general,
how often do you see members of your extended family (or relatives not living with
you) in person?” Responses were coded on a six-point scale where 1 represents
“never” and 6 represents “very often”. Using a similar scale, respondents were also
asked the question: “In general, how often do you make time to keep in touch with
friends?” Our measures of social networks are based on responses to these questions.
To examine the role of consumption choices as a potential channel we use the HILDA
variable that captures household expenditure on meals eaten outside the home.
Descriptive statistics of all the variables are presented in appendix Table A4.1.
20
This data is publicly available at https://www.fuelwatch.wa.gov.au/
108
4.4
Empirical Method
Given that we have individual-level survey data on SWB and monthly city-level petrol
prices over the period 2001—2017, we begin our analysis by establishing an empirical
relationship between monthly petrol prices and self-reported life satisfaction in the
month of interview. We estimate versions of the following standard reduced form
regression model:
′
′
+ ϑi + φc + ρm + τt + εi,mct
SWBi,mct = α0 + βPmct + γXict
+ λSct
(4.1)
where SWBi,mct is the life satisfaction of individual i in city c in month m at time t.
The month corresponds to the participant’s month of interview, while time corresponds
with the year of each wave of the HILDA survey. P represents real monthly unleaded
petrol prices for each city at time t while the vector 𝐗 ′ict captures a number of
′
demographic controls correlated with SWB. The model also includes a vector 𝐒ct
which represents state-level covariates – per capita income and population density. We
also include in our model ϑ which controls for time invariant unobserved individual
characteristics and city-fixed effects φ to account for permanent differences across
cities (e.g., average fuel efficiency of vehicles, and access to public transportation) that
may simultaneously affect petrol prices and SWB. ρ in our model controls for monthly
fixed effects to account for seasonal variations (e.g., changing monthly weather
patterns) and τ are year dummies which are included to account for time-varying
aggregate trends influencing petrol prices and wellbeing over time (e.g., government
policies affecting the entire economy, natural disasters and international political
unrest). α and ε are respectively, the constant and error term in the model.
In our baseline model, to estimate equation (4.1) we use pooled ordinary least squares
(POLS) and, exploiting the panel structure of the data, panel fixed effects to control
for time-invariant characteristics of individuals that are typically not observed that
confound estimates of causal effects with this kind of survey data. SWB can be treated
as cardinal or ordinal. Ferrer-i-Carbonell and Frijters (2004) show that the findings are
not sensitive to treating measures of wellbeing as cardinal or ordinal. In our main
results, we treat SWB as cardinal, but in the robustness checks we test the sensitivity
of our findings to treating SWB as being ordinal.
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The error term in equation (4.1) may include other variables that are difficult to control,
but may be correlated with petrol prices, resulting in either overestimation (upward
bias) or underestimation (downward bias) of our baseline estimates due to omitted
variables, simultaneity bias and measurement error. In our case, an example of an
omitted variable for which we are unable to control is the time spent driving. Driving
time and petrol prices may be negatively correlated because increased driving time
could mean that people who drive more are able to get lower average fuel prices as
they pass more petrol stations on their journey and, as a result, are able to benefit from
a wider range of fuel price variation (Yatchew & No, 2001), which enhances their
SWB. Some studies, though, suggest that longer commuting or driving time to work
adversely effects SWB (see for e.g. Lorenz, 2018; Zhu, Li, Chen, Liu & Zeng, 2019),
while time spent driving for family getaways or sight-seeing has a positive effect on
life satisfaction (Morris, 2015). Hence, although the estimator will not be consistent
due to the correlation between the error term and price, intuitively increased driving
time could lead to either underestimation or overestimation in the true relationship,
and thus, on balance, the overall direction of bias from omitted variables cannot be
precisely predicted.
Another potential source of endogeneity comes from the fact that petrol prices might
suffer from measurement error. Fernandez-Blanco, Orea and Prieto-Rodriguez (2013)
use a theoretical model to show that average prices are imperfect proxies for the
underlying price and that the use of average prices introduces measurement errors,
even when the original prices may be exogenous. The third source of endogeneity
comes from simultaneity bias. For instance, happier people may spend more time with
their family and friends and, as a result, make more effort to see them frequently.
Increased visits to maintain social networks would intuitively mean travelling often
allowing people to benefit from price variations and as a result, pay less for petrol.
This will understate the true extent of petrol prices, suggesting a downward bias in the
OLS and FE estimates. Overall, given the combination of potential measurement
errors; omitted variable and simultaneity bias, it is difficult to state the general
direction of bias with certainty, but we suggest that the overall direction of bias would
come from underestimation that will result in a downward bias in the baseline
estimates.
110
Our main identification strategy to address endogeneity is to instrument for petrol
prices using the Arca Oil Stock prices index, which is price-weighted index of leading
companies involved in the exploration, development and production of oil listed on
the NYSE. This index proxies the performance of the oil industry, which ultimately
influences oil and petrol prices globally. To serve as a good instrument, the NYSE
Arca Oil Stock prices index should be correlated with petrol prices and be orthogonal
to the error term in Equation (1). Intuitively, we expect that stock prices of the world’s
major oil suppliers will be correlated with petrol prices. However, movements in
NYSE Arca Oil Stock prices are unlikely to be directly related to the SWB of
participants in the sample. If participants hold shares in NYSE Arca Oil Stocks,
movements in these stocks would have a direct effect on their SWB, but this is
unlikely.
While there are no data, of which we are aware, on the proportion of Australians who
hold shares in NYSE Arca Oil Stocks, a 2017 survey by Deloitte Access Economics
(2017) found that just 8 per cent of Australians held shares listed on stock markets
outside Australia. Moreover, as the survey acknowledged, this likely represents an
upper bound estimate because some participants may have interpreted the question as
asking if they held shares in international companies listed on the Australian Stock
Exchange (Deloitte Access Economics, 2017, p.4). Thus, the proportion of Australians
holding shares on the NYSE, and specifically in NYSE Arca oil Stocks, is likely to be
very low.
Another potential threat to the exogeneity condition is that movements in NYSE Oil
Stock could influence movements in oil stocks on the Australian Stock Exchange and,
thus, influence the SWB of individuals holding these shares. However, findings
concerning the relationship between the US and Australian stock markets have, at best,
been mixed. Valadkhani and Chen (2014) find that stock market volatility in Australia
is Granger caused by US stock market volatility, but Allen and MacDonald (1995),
Narayan and Smyth (2004) and Roca (1999) find that there is no long-run relationship
between the Australian and US stock markets. Even if one accepts that movements in
the US market moves the Australian market, in 2017 less than one third (31 percent)
of Australians owned shares (Deloitte Access Economics, 2017). There are no
questions in HILDA that specifically ask participants if they own shares, although, in
111
each wave of the HILDA survey, participants were asked if they “received income
from dividends”. Responses to this question is an upper bound estimate on if they own
shares. Responses were coded as “received” or “did not receive” income from
dividends. Over all waves, those reporting that they received dividends ranged from
16 to 28 percent of participants, slightly less than the figure reported in the Deloitte
Access Economics report. It is likely that most of these participants typically held very
small parcels of shares. Deloitte Access Economics (2017) found that most Australians
who held shares were “mum or dad investors”, who held a small number of shares in
one or two privatized former government-owned companies, such as Qantas and
Telstra. Thus, overall it is unlikely that movements in the NYSE Arca Oil price index
would influence the SWB of participants through the Australian stock market.
Movements in the Dow Jones Industrial Average are reported in the Australian media.
Hence, conceivably it is also possible that movements in the US stock market might
be a proxy for the state of the economy more generally and, in this sense, have an effect
on the SWB of Australians irrespective of whether they own shares. Frijters, Johnson,
Shields and Sinha (2015), also using HILDA, examine whether the Australian and US
stock market directly affects the SWB of Australians. While they find that movements
in the Australian stock market influences the SWB of Australians, they find that
movements in the Dow Jones Industrial Average only has a weak effect (at 10 percent)
on the SWB of Australians and only for males. Moreover, when movements in the All
Ordinaries are controlled for in the same specification, the effect of the Dow Jones
Industrial Average on SWB becomes insignificant. Given that the NYSE Arca Oil
price index is much narrower in its coverage and is virtually unreported in the
Australian media, it is very unlikely that, first, many Australians would even be aware
of it and, second, that movements in it would impact on their SWB, unless they held
oil stocks.
It is important to be clear here about our source of variation. Our petrol price data is at
the city-level and at monthly frequency. Given that we have information on the specific
month of each year in which respondents were interviewed in the HILDA survey, we
take advantage of this information and match petrol price information against the year
and month of interview of each respondent. We also do the same for our instrument,
the NYSE Arca Oil Stock prices, which is available at the monthly frequency as well.
112
Thus, while individuals may live in the same city, we still observe variations in our
observations because these individuals may be interviewed in different months, in
which petrol prices may be different.
For example, take two participants, one of whom lives in Melbourne and the other in
Sydney. Assume that in 2015, the Melbourne participant was interviewed in February
and the Sydney participant was interviewed in March and that in 2016 the Melbourne
participant was interviewed in March and the Sydney participant was interviewed in
May. The variation comes from the fact that they faced differently monthly petrol
prices and, hence, the effect of oil prices on petrol prices will vary across both
individual/cities and time.21
As we employ monthly NYSE Arca Oil Stocks prices as our IV, participants
interviewed in different months in a given year will face different stock prices;
however, participants interviewed in the same month in a given year will face the same
stock price, irrespective of the city in which they live. An important check on the
validity of our instrument, hence, is that the variation in any characteristics correlated
with the timing of interview at the city-month-level, such as weather conditions, are
not correlated with NYSE Arca Oil Stocks prices. As a check we link the average
maximum temperature at the city-month level22 to the individual’s month of interview
and then regress average temperature on the IV using Equation (4.1) with a full set of
controls. The results for this test are presented in appendix Table A4.2. The coefficient
on the NYSE Arca Oil price index is insignificant in both the POLS and FE
specification, suggesting that the NYSE Arca Oil Stocks prices are a valid IV.
As a robustness check, we use Dated Brent crude oil prices as an alternative instrument
for petrol prices. Petrol prices in Australia are directly influenced by international
crude oil prices given that Australia imports almost all of its refined petroleum
(Commonwealth of Australia, 2019). While there are a number of widely used
international benchmark prices such as Dubai, Dated Brent, Nigerian Forcados and
21
This example would also hold if both participants lived in Melbourne or both participants lived in
Sydney because petrol prices obviously differ from month to month within the same city.
22
The data on temperature, which is publicly available is sourced from the Bureau of Meteorology,
Australia at http://www.bom.gov.au/climate/data/index.shtml
113
West Texas Intermediate (WTI), Dated Brent crude oil is the most relevant benchmark
for the price of petrol and diesel in Australia.23 Amadeo (2019) documents that the
crude oil price represents the major component of the price of petrol with the rest
dependent on refinery and distribution costs, company profits and government taxes.
Given that taxes and profit margins largely remain stable, the daily change in petrol
prices tend to reflect crude oil price fluctuations. However, movements in crude oil
prices are unlikely to be directly related to the SWB of any individual in the sample.
Thus, if crude oil prices change, the only mechanism via which such changes will
affect SWB will be through petrol prices.
Despite our arguments above that, for the participants in the HILDA survey, it is
unlikely that either NYSE Arca Oil Stocks prices or Dated Brent crude oil prices will
directly affect SWB, one may still be concerned that the exclusion criteria will not be
satisfied. As a further sensitivity check, we also adopt the Lewbel (2012)
heteroskedasticity based approach which does not require any exclusion restriction to
be satisfied. This method uses the presence of heteroskedasticity as a precondition for
identification to construct internally generated instruments based on a heteroskedastic
covariance restriction. This approach has been used in several studies as a robustness
check on the findings with external instruments (see for e.g. Awaworyi Churchill &
Smyth, 2019; Lewbel, 2012; Mishra & Smyth, 2015).
In Section 4.2 we argued that petrol prices influence SWB through channels related to
leisure activities and consumption choices. While it is difficult to isolate, and test, the
role of all potential channels, we examine the role of social networks and consumption
choices. For factors such as eating outside the home and maintaining contact with
family and friends to qualify as potential channels linking petrol prices to SWB, in
addition to being correlated with petrol prices, they should also be correlated with
SWB and their inclusion as additional covariates in the regression linking SWB to
petrol prices should decrease the magnitude of the coefficient on petrol prices or render
it statistically insignificant (Alesina & Zhuravskaya, 2011). To examine the role of
23
See the Australian Institute of Petroleum website https://aip.com.au/pricing/internationalprices/international-market-watch for a discussion of Dated Brent crude oil as the relevant benchmark
for Australia. In results that are not reported we also instrumented for petrol prices using Dubai, Nigerian
Forcados and WTI and the results were the same reflecting very high correlation between alternative
international benchmark prices.
114
these factors, consistent with the literature (see e.g., Powdthavee & Wooden, 2015),
we adopt a multiple mediation method using a structural equation model (Baron &
Kenny, 1986), that also allows us to understand how much of the effects of petrol
prices on SWB can be explained by its effects on the potential channels or mediating
factors (i.e., the indirect effects of petrol prices). The multiple mediation method
allows us to estimate how much of the indirect relationship between petrol prices and
SWB is channelled through social networks, and how much is channelled through
household expenditure on meals eaten out. In addition to isolating the indirect and
direct effects of petrol prices taking into account the potential channels, the use of a
structural equation model has the added advantage of allowing errors to be correlated
across individual models with the system of equations.
4.5
4.5.1
Results
Baseline results
Table 4.2 presents the baseline results for equation (4.1), in which we estimate the
relationship between petrol prices and SWB. Each column presents coefficients, robust
standard errors (in parentheses) and standardised coefficients (in brackets) associated
with petrol price and SWB, in which we progressively add more controls. In columns
(1) and (2), we use POLS and panel fixed effects respectively to examine the
relationship between petrol prices and SWB with only demographic controls. Statelevel controls are added in columns (3) and (4) and city-level fixed effects are added
in columns (5) and (6). We are using monthly petrol prices to match the SWB of
participants in the month in which they were interviewed over time. Thus, in our
preferred specification, in columns (7) and (8) we add month fixed effects to capture
seasonality, that is regular and predictable each year and can be linked with a specific
time of year, and year fixed effects, that capture annual time trends and year to year
variations, together with a full set of controls, state-level controls and city-level fixed
effects. The control of both month and year fixed effects in the same specification are
particularly important given that they each play unique roles. Given that month fixed
effects are regular and predictable from year to year, they capture seasonal variations
within a year. The Australian summer is in December to February when it is very hot
and there are summer holidays. The Australian winter is in June to August when it is
relatively cold. The month effects are controlling these seasonal effects on SWB,
depending on when the respondent completed the survey. The month fixed effects,
115
though, are not able to capture shocks caused by episodic events that extend over
prolonged periods and occur irregularly in some years, but not others, such as financial
crises or a pandemic. All specifications are estimated with cluster-robust standard
errors at the individual level.
We find a negative association between petrol prices and SWB in all cases. In our
preferred specifications, the coefficient on petrol prices is negative with an effect size
of 0.1092 using POLS and 0.1137 using panel fixed effects respectively. This suggests
that, on average, individuals who face a one dollar per litre increase in the petrol price
have 0.1092—0.1137 lower life satisfaction on a 0—10 scale. Between 2016 and 2018
Australia experienced an annual average increase of 14.02 cents per litre, which
corresponds with a reduction in life satisfaction scores between 0.0153 and 0.0159 on
a 0—10 scale. These point estimates though appear small in magnitude, intuitively
make sense, especially given that SWB does not vary very much. Boyd-Swan and
Herbst (2012) find reduction in life satisfaction scores by 0.048 on a 1—6 scale for a
one dollar per gallon increase in price of gasoline in the US.24 In terms of the
standardised coefficients, in our preferred specification the POLS results suggest that
a one standard deviation increase in petrol prices is associated with a 0.0115 standard
deviation decline in SWB, while the panel fixed effects results suggest that a one
standard deviation increase in petrol prices is associated with a 0.0120 standard
deviation decline in SWB.
In Table A4.3, in the appendix, we present the full results for the POLS and panel fixed
effects models with a full set of controls (columns 7 and 8 in Table 4.2). The signs and
significance of the covariates are generally consistent with the existing SWB literature
(see Dolan et al., 2008). We find a U-shaped relationship between age and SWB with
the minimum occurring around the ages 40—45, females have higher SWB than males
while those who have more dependents in the family have lower SWB. Those who are
24
For a $1 per gallon increase in the price of petrol, our estimates equate to a 0.4133-0.4304 decline in
SWB on a 1-10 scale. Boyd-Swan and Herbst (2012) measure SWB on a 1-6 scale. For a $1 per gallon
increase in the price of petrol, our estimates equate to a 0.2474-0.2577 decline in SWB on a 1-6 scale.
Hence, our estimates for the effect of petrol prices on SWB are considerably higher than those in BoydSwan and Herbst (2012).
116
married and have higher income have higher SWB, while those individuals with a
long—term illness have lower SWB.
4.5.2
Addressing endogeneity
In Table 4.3, we present the 2SLS results for the same specifications as reported in
Table 4.2, in which we instrument for petrol prices using the NYSE Arca Oil Stocks
price index. The first stage results suggest that the NYSE Arca Oil Stocks price index
is positively correlated with petrol prices. This implies that an increase in oil stock
prices have a significant and positive effect on the city–level petrol price. The first
stage F-statistics are greater than 10 and R-squared from the first stage regression is
relatively high in each case, suggesting that our instrument is relevant.
The results in Table 4.3 suggests that there is substantial downward bias in our baseline
estimates due to endogeneity as the 2SLS estimates are relatively larger in size than
both the POLS and panel fixed effects estimates. Our preferred POLS estimate in
column 7 suggests that a one standard deviation increase in the petrol price leads to a
0.0245 standard deviation decline in SWB. After controlling for individual fixed
effects, our preferred panel fixed effects estimate in column 8 suggest a slightly smaller
effect, whereby a one standard deviation increase in the petrol price is associated with
a decline in SWB of 0.0157 standard deviations. We present the full results for
columns 7 and 8 in Table A4.3 in the appendix. The coefficients on all other variables
in the 2SLS and panel fixed effects-IV models are similar to the baseline.
4.5.3
Potential channels through which petrol prices influence SWB
We next present the potential channel analysis focusing on the role of social networks
and consumption choices, proxied by eating out. A large body of literature emphasises
the importance of social networks in promoting SWB (see for e.g., Ateca-Amestoy,
Aguilar & Moro-Egido, 2014; Awaworyi Churchill & Mishra, 2017; Duckitt, 1982;
Elgar et al., 2011; Portela, Neira & Salinas-Jiménez, 2013). This literature shows that
good social relationships and networks are valuable and can make people happy, thus
increasing their overall wellbeing. Such networks can avert conflict, avoid
psychological deprivation and improve one’s ability to cope with stress, thus
promoting wellbeing (Biswas-Diener & Diener, 2006). Hence, we expect an increase
117
Table 4.2
Variables
Petrol prices and subjective wellbeing, using city-level monthly ULP price data (baseline results)
(1)
Pooled OLS
(2)
Panel FE
(3)
Pooled OLS
(4)
Panel FE
(6)
Panel FE
(7)
Pooled OLS
(8)
Panel FE
-0.0542***
-0.0827***
-0.0575***
-0.0964***
-0.0644***
-0.1092***
-0.1137***
(0.0233)
(0.0263)
(0.0234)
(0.0261)
(0.0236)
(0.0365)
(0.0414)
[-0.0057]
[-0.0087]
[-0.0061]
[-0.0102]
[-0.0068]
[-0.0115]
[-0.0120]
Demographic controls
Yes
Yes
Yes
Yes
Yes
Yes
Yes
State-level controls
No
Yes
Yes
Yes
Yes
Yes
Yes
City FE
No
No
No
Yes
Yes
Yes
Yes
Monthly FE
No
No
No
No
No
Yes
Yes
Yearly FE
No
No
No
No
No
Yes
Yes
Observations
118,342
118,342
118,342
118,342
118,342
118,342
118,342
R-squared
0.0135
0.0825
0.0135
0.0838
0.0137
0.0842
0.0142
Number of Individuals
14,953
14,953
14,953
14,953
Notes: The dependent variable is life satisfaction which is measured on a scale of 0-10, where 0 is totally dissatisfied and 10 is totally satisfied. Demographic control variables
consist of gender (only included in pooled OLS specification as it is time-invariant), age, age-squared, marital status (never married or de-facto, widowed, divorced, separated,
de-facto, legally married), income, employment status (employed, unemployed including those not in the labour force), level of education (year 12 & below, certificate, diploma,
bachelor or honours, graduate diploma, postgraduate), health status (long term health issues, no long term health issues) and number of dependents. State-level control variables
include population density and real GDP per capita by state. Panel FE regressions also control for individual fixed-effects. Robust standard errors are in parentheses. Individual
clustered standard errors are reported for FE models. Standardised coefficients in brackets. *** p<0.01, ** p<0.05, * p<0.10
Petrol price
-0.0797***
(0.0263)
[-0.0084]
Yes
No
No
No
No
118,342
0.0823
(5)
Pooled OLS
118
Table 4.3
Petrol prices and subjective wellbeing, using city-level monthly ULP price data (IV results)
Variables
Petrol price
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R-squared
Number of Individuals
First stage
Instrument:
NYSE Arca Oil Stock price index
R-squared
F-Statistics
Notes: see notes to Table 4.2.
(1)
2SLS
(2)
Panel FE-IV
(3)
2SLS
(4)
Panel FE-IV
(5)
2SLS
(6)
Panel FE-IV
(7)
2SLS
(8)
Panel FE-IV
-0.3570***
(0.0525)
[-0.0376]
Yes
No
No
No
No
118,342
0.0814
-0.1353***
(0.0443)
[-0.0083]
Yes
No
No
No
No
118,342
0.0135
14,953
-0.3608***
(0.0505)
[-0.0380]
Yes
Yes
No
No
No
118,342
0.0816
-0.1276***
(0.0408)
[-0.0083]
Yes
Yes
No
No
No
118,342
0.0136
14,953
-0.2365***
(0.0400)
[-0.0249]
Yes
Yes
Yes
No
No
118,342
0.0835
-0.1185***
(0.0353)
[-0.0086]
Yes
Yes
Yes
No
No
118,342
0.0137
14,953
-0.2324***
(0.0617)
[-0.0245]
Yes
Yes
Yes
Yes
Yes
118,342
0.0844
-0.1566***
(0.0517)
[-0.0157]
Yes
Yes
Yes
Yes
Yes
118,342
0.0143
14,953
0.0003***
(0.0000)
0.3391
>10
0.0003***
(0.0000)
0.3391
>10
0.0003***
(0.0000)
0.3764
>10
0.0003***
(0.0000)
0.3764
>10
0.0004***
(0.0000)
0.4607
>10
0.0004***
(0.0000)
0.4607
>10
0.0005***
(0.0000)
0.5840
>10
0.0005***
(0.0000)
0.5840
>10
119
in petrol prices to have a negative effect on maintaining social networks and that the
negative effect on maintaining social networks to be reflected in lower SWB.
Another strand of studies examines the role of eating behaviour and consumption
choices on SWB (see for e.g. Blachflower, Oswald & Stewart-Brown, 2013; Holder,
2019; Huffman & Rizov, 2017; Legyel, Tate & Blatz, 2009; Schnettler, Lobos et al.,
2017; Schnettler, Miranda et al., 2015; Schnettler, Pena et al., 2013). We expect an
increase in petrol prices to have a negative effect on propensity to eat out, but the effect
of eating out less on SWB is ambiguous. Eating out less could have a positive effect
on SWB (avoiding calorie foods and eating homemade healthy foods promotes SWB)
or a negative effect on SWB (to the extent that eating out has a social dimension, eating
out less reduces social connections, adversely affecting SWB).
Table 4.4 Estimated indirect and direct effects of petrol prices on subjective
wellbeing
Mediating variables
Social networks outside the home
Community participation: See members of extended family
Community participation: Keep in touch with friends
Eating out
Log of household expenditure on meals eaten out
Total indirect effect
Direct effect
Combined effect (total indirect effect + direct effect)
Observations
Petrol price
-0.0063***
(0.0024)
-0.0072***
(0.0033)
0.0001
(0.0003)
-0.0134***
(0.0048)
0.0289
(0.0239)
0.0155
(0.0246)
11,208
Notes: The coefficients are standardised coefficients. Bootstrapped standard errors (200) replications are in
parenthesis. *** p<0.01, ** p<0.05, * p<0.10. The model includes demographic controls and includes fixed effects
at city and monthly levels. Community participation: See members of extended family is the individual’s response
to the question ‘In general, how often do you do the following things: See members of your extended family (or
relatives not living with you) in person. This questionnaire was asked in wave 6, 10 and 14 only. Community
participation: Keep in touch with friends is the individual’s response to the question ‘In general, how often do you
do the following things: Make time to keep in touch with friends. This questionnaire was asked in wave 6, 10 and
14 only. Log of household expenditure on meals eaten out is the log of monthly household expenditure on meals
eaten out. This information was collected from waves 6—17. Hence, to include the three potential mediators
together, the SEM specification is based on waves 6, 10 and 14 only.
120
A summary of the indirect effects of petrol prices through the three potential channels
are reported in Table 4.4. We find that an increase in petrol price is negatively
associated with both measures of social networks, while the effects on household
expenditure on meals eaten out is statistically insignificant.25 The total indirect effect
of petrol price is negative and significant. The results also show that with the inclusion
of the potential channel variables, the direct effect of petrol price on SWB becomes
statistically insignificant.
These
results
suggest
that
the
social
network
variables mediate the relationship between petrol prices and SWB.
4.5.4
Extension and robustness checks
In this section, we conduct a series of checks and extensions to examine the robustness
of our results. We first extend our analysis to examine the heterogenous effects of
petrol price across various sub-groups. We then examine how petrol price volatility
effects the hypothesised relationship between petrol prices and SWB. We also examine
the short– and long–run dynamics of petrol prices and the economic significance of
this association. Third, we examine the robustness of our results to using Dated Brent
an alternative instrument, as well as the Lewbel (2012) 2SLS approach. Finally, we
examine the sensitivity of our results to alternative ways of measuring SWB and fuel
prices as well as perform other sensitivity checks.
4.5.4.1 Heterogenous effects across sub–groups
In Figure 4.2, we show the relationship between petrol prices and SWB for sub–
samples of males, females, age groups, education level, employment status, income
level, marital status, having children and the season in which the respondent was
interviewed. The estimates are the predictive margins of petrol prices at an increment
of every $0.10 between the lowest and highest recorded real petrol prices over the
sample period for each sub-group. The results suggest that an increase in petrol prices
is associated with lower SWB for all subgroups.
25
Traditionally women have shouldered the responsibility for preparing food at home. According to the
2016 Australian census, the average Australian woman spends up to 14 hours a week cooking and
cleaning, while the average man does fewer than five hours and 26 percent of men do no cooking at all
(ABS, 2016). This means that there are real time and labor costs associated with eating meals prepared
at home, especially for women. If meals are increasingly prepared at home, women bear the brunt of
this labor and, therefore, may be disproportionately influenced in terms of decreased SWB. To examine
if this is the case we performed the mediation analysis reported in Table 4.4 separately for each gender
(results not reported). The indirect effect of eating out on SWB is insignificant for both men and women.
121
Figure 4.2 Heterogeneous effects of petrol price on life satisfaction by subgroups
Note: All figures reported here are based on regression estimates using the same model specification in
Column 7 of Table 4.2 but accounting for the different sub-groups.
122
While the effect of petrol prices on the SWB of both males and females is negative,
the effect is stronger for males than females. This finding is consistent with a higher
proportion of men than women have driver licenses in Australia (Loader, 2015) and,
as result, being more likely to be the ones filling up at the pump. That male labour
force participation rates are higher than female labour force participation rates in
Australia (Australia Bureau of Statistics, 2018), combined with the fact that many
households are located in the outer suburbs, mean that males are also more likely than
females to be making long daily commutes in the car to go to work. These results are
consistent with Boyd-Swan and Herbst (2012) who find that women’s wellbeing is not
sensitive to gasoline price changes in the US.
In terms of age groupings, petrol prices have the strongest association with SWB for
those over the 64 years of age followed by those in the mid-age category (between 35
and 64 years). The findings for those aged over 64 likely reflect that most people in
this category are no longer working and are living on a relatively low, fixed income,
that makes them particularly sensitive to price increases. These people are not
excessively engaged in commuter behaviour and their response to rising petrol prices
is likely to be to simply drive less and to condense errands into single trips, which
reduces their SWB. This is consistent with Harrison and Ragland (2003) who find that
reduced driving activities has adverse consequences on individuals’ life satisfaction.
Those in the 35—64 age group form the bulk of families living in the outer suburbs of
the large cities that make long commutes to work each day. Meanwhile, those in the
relatively young age group (between 18 and 34 years) appear to be least affected by
rising petrol prices as the impact on their SWB is very small in magnitude. The results
for those aged 18—34 are consistent with a recent study of car use in Melbourne by
Jain, Rose and Johnson (2018), who find that those aged in their twenties and thirties
have become habituated to having ready car access and heavily discount the costs
associated with maintaining and owning a car.
The impact of petrol prices on life satisfaction by employment status, income level,
marital status and having children differs among categories in these groups. Those who
are unemployed, have income below median income levels, are married and have
children experience a greater decline in SWB, in response to rising petrol prices. Each
of these groups of people have a relatively lower income and/or face a higher
123
opportunity cost of driving when petrol prices increase, which can be expected to make
them particularly sensitive to price increases. As discussed above, urban sprawl,
combined with poor public transport options, in most Australian cities, creates a
problem of ‘forced car ownership’26 (Currie et al., 2018). This phenomenon lends
support to our findings that the adverse effect of petrol prices on the SWB of those
below the median income is stronger than those otherwise.
However, there appears to be no significant difference in the effect of petrol prices on
the SWB of individuals with different level of education attainment. In a study
identifying factors influencing the adoption of vehicle sharing systems in Greece,
Efthymiou, Antoniou and Waddell (2013) find that one’s level of education was not
an important consideration. This is likely to be true in our context as well given the
strong car ownership culture in Australia (Kent, 2018), which implies most people own
a car, irrespective of their education level.
Following Welsch and Biermann (2017), at the bottom of Figure 4.2, we examine if
there is a difference in the effect of petrol prices on SWB across different seasons. To
do this, we group the months from September to February as hot months, reflecting
the spring and summer season and the months from March to August as the cooler
months, reflecting the fall and winter months in Australia. The estimates show that
individuals interviewed in the hotter months are significantly negatively affected by
increase in petrol prices. Those effects on wellbeing for those interviewed in the cooler
months are negative, but insignificant. These results are not surprising as in the
summer months most families in Australia take holidays which often involve long road
trips and it is common for petrol stations to increase prices.
4.5.4.2 Role of volatility and lagged effects of petrol price on SWB
Numerous studies have identified that economic activity responds differently to
absolute levels and variations in real oil prices (see for e.g. Blanchard & Gali, 2007;
Cunado & Gracia, 2005; Kilian, 2009; Mohaddes & Pesaran, 2017). There are also a
few studies that have analysed individual behavioural changes due to fuel price
volatility. Studies, largely for the United States (see for e.g. Lane, 2010; Smart, 2014),
‘Forced car ownership’ is a term used to describe the situation, in which low income households have
little choice, but to own and use cars for mobility because there are few alternatives available.
26
124
find that fuel price variations are a meaningful driver of consumer behavioural change.
Smart (2014) argues that individuals are likely to respond to price changes largely by
using some reference price established through repetitive purchasing against which
they judge price fluctuations. In Table 4.5 we examine how fluctuations in petrol prices
are associated with individual’s assessment of their SWB.27
In panel A and B of Table 4.5, we evaluate how individuals respond to the petrol price
they faced in the month of their interview, conditional on the petrol price in the month
prior to the interview in a given year. In panel A, the 2SLS and panel FE-IV results
suggest that petrol prices have a significant adverse effect on the SWB of those who
faced a higher petrol price in their month of interview, compared to the month prior to
the interview. In panel B, however, petrol prices have an insignificant effect on SWB
for those for whom petrol prices in their month of interview were lower than in the
month immediately prior to the interview.
In panel C of Table 4.5 we use a simple GARCH(1,1) process to obtain monthly
conditional standard deviation, in order to examine the effect of monthly petrol price
volatility on SWB. We use this volatility measure instead of petrol prices in the 2SLS
and panel FE-IV specifications and find that petrol price volatility has a negative and
significant effect on SWB. The estimates suggest that a one standard deviation increase
in petrol price volatility leads to a decline in SWB between 0.0377 and 0.0582 standard
deviations. In particular, these effects are almost three times the magnitude of an
increase in absolute petrol prices which suggests that volatility in petrol prices has an
important adverse effect on SWB. This result is consistent with Smart (2014) who
argues that consumers view fuel price volatility as an indication of things to come and
that rapid fuel price fluctuations have greater emotional impact on consumers.
In panel D and E of Table 4.5, we separate our sample into those facing upward
volatility and those facing downward volatility in petrol prices during the month in
which they were interviewed in the given year of the survey, based on the volatility
variable used in panel C. In panel D, the 2SLS and panel FE-IV results suggest that
27
An alternative approach to examine the differences across difference sub-samples is to use interaction
terms, however, such interaction terms are likely to be endogenous. Thus, we split our sample and
instrument for petrol prices in each sub-sample regression.
125
Table 4.5
Lagged petrol prices, petrol price volatility and subjective wellbeing
Variables
2SLS
Panel FE-IV
Panel A: Current month price >= Last month price
Petrol price
-0.4122***
-0.2721***
(0.0995)
(0.0773)
[-0.0431]
[-0.0300)]
Observations
55,759
55,759
Panel B: Current month price < Last month price
Petrol price
-0.0667
-0.0625
(0.1144)
(0.0423)
[-0.0065]
[-0.0058]
Observations
62,583
62,583
Panel C: Impact of monthly price volatility
Petrol price volatility
-1.2543***
-0.8873***
(0.3334)
(0.2962)
[-0.0582]
[-0.0377]
Observations
118,342
118,342
Panel D: Impact of monthly price volatility: Upward volatility
Petrol price volatility
-0.2632***
-0.3004***
(0.0960)
(0.0936)
[-0.0288]
[-0.0300]
Observations
55,949
55,949
Panel E: Impact of monthly price volatility: Downward volatility
Petrol price volatility
-0.0642
0.0521
(0.1406)
(0.0432)
[-0.0065]
[0.0049]
Observations
62,393
62,393
Panel F: Impact of lagged monthly prices
Petrol prices: contemporaneous
-0.3076***
-0.1559***
(0.0713)
(0.0592)
[-0.0332]
(-0.0161]
0.1967*
(0.1029)
[0.0206]
Petrol prices: 1-month lag
Petrol prices: 2-month lag
-0.0094
(0.0455)
[-0.0010]
0.0029
-0.0222
(0.1017)
(0.0449)
[0.0003]
[-0.0021]
Observations
89,357
89,357
Panel G: Current month price >= Average yearly city-level price
Petrol price
-0.4588***
-0.2848***
(0.0849)
(0.0710)
[-0.0496]
[-0.0300]
Observations
60,468
60,468
Panel H: Current month price < Average yearly city-level price
Petrol price
-0.0857
-0.0353
(0.0833)
(0.0866)
[-0.0080]
[-0.0030]
126
Observations
57,874
Panel I: Impact of yearly city-level price volatility
Petrol price volatility
-0.6094***
(0.2350)
[-0.0135]
Observations
118,342
57,874
-0.2982*
(0.1705)
[-0.0058]
118,342
Notes: All models include demographic and state-level controls and includes fixed effects at city,
monthly and yearly levels. In Panel C, a simple GARCH (1,1) process is used to obtain the conditional
standard deviation as the measure of monthly volatility in petrol prices. This monthly petrol price
volatility variable is then instrumented using the NYSE Arca Oil Stock prices index as the IV. In Panels
D and E, the monthly volatility variable, as used in Panel C, is used to create a dummy variable denoting
1 if the volatility is higher than last month’s volatility and 0 otherwise. This dummy variable is then
used to separate the sample into those facing upward volatility and downward volatility during their
month of interview in the given year of survey. In Panel I, volatility for each year is calculated based
on the standard deviation of the petrol price over the 12-month period in that year. This yearly petrol
price volatility variable is then instrumented using the NYSE Arca Oil Stock prices index as IV. The
NYSE Arca Oil Stock prices index is used as the IV in all model specifications.
upward volatility in petrol prices has a significant adverse effect on SWB. The
estimates show that a one standard deviation increase in petrol price volatility for those
who face higher price volatility leads to decline in SWB between 0.0288 and 0.0300
standard deviations. However, the results for downward volatility are insignificant.
In panel F of Table 4.5 we present results in which we incorporate two–month lags in
petrol prices in equation (4.1). The two–month lags allows us to capture the effect of
petrol price cycles, given that price cycles in Australian capital cities typically range
from a low of two weeks to a high of about two months (ACCC, 2019). The 2SLS
estimates suggest that although a contemporaneous increase in petrol prices
significantly reduces SWB, the losses are mildly offset by an increase in SWB after
one–month. However, the panel FE-IV estimates suggest that only current month
petrol prices have a significant adverse effect on SWB. The coefficient on the two—
month lag in both specifications are small in magnitude and statistically insignificant.
Together, the lags in the panel FE-IV estimates suggest that after two months, a
sustained $1 per litre increase in petrol prices leads to 0.1875 points lower life
satisfaction on a 0—10 scale, an estimate that is about a fifth larger than the estimate
in column 8 of Table 4.3.
In panel G and H of Table 4.5, we perform a similar exercise to what we did in panel
A and B, but instead we use average yearly city–level prices to account for the
possibility that individuals might use average yearly prices as a reference price to
127
respond to petrol price changes. In this exercise, we match current monthly–level
petrol prices to average petrol price faced by individuals in their city. In panel G, the
2SLS and panel FE-IV results suggest that the petrol price has a significant adverse
effect on the SWB of those individuals who faced higher petrol price in their month of
interview, compared to the annual average petrol price in their city. Conversely, results
in panel H suggest that for those individuals who faced lower petrol prices in their
month of interview, relative to the average annual price, petrol prices have an
insignificant effect on their SWB. These results indicate that irrespective of the
reference price used, petrol prices have a significant adverse effect on the SWB of
those who faced a higher petrol price in their month of interview, compared to the
month prior to the interview.
Finally, in panel I of Table 4.5 we calculate the standard deviation of petrol prices over
the 12—month period to obtain an alternative measure of price volatility. We find that
petrol price volatility has a negative and significant effect on SWB in both the 2SLS
and panel FE-IV results. The estimates suggest that a one standard deviation increase
in petrol price volatility leads to a decline in SWB of between 0.0058 and 0.0135
standard deviations.
4.5.4.3 Economic significance of petrol price effects
We estimate the economic significance of the effects of petrol price changes by
calculating the income equivalence of the drop in SWB due to an increase in petrol
prices. To do so, we first calculate how much monthly income the median family
would need in order to offset the reduction in SWB from rising petrol prices and then
compare this amount to the effect of an increase in unemployment on SWB. In Table
4.6, we present the income equivalence of a one standard deviation increase in petrol
prices in the first panel followed by a one standard deviation increase in the
unemployment rate in the second panel. A one standard deviation increase in petrol
prices equate to $0.1547 per litre over the 2001–2017 period, while a one standard
deviation increase in the unemployment rate is a 0.92 percentage points over the same
period.
A $0.1547 per litre increase in petrol prices produces a reduction in SWB which is
equivalent to a loss of $AUD538 in monthly household income. When compared to
128
the reported household income in the HILDA survey, this corresponds to 7.3 percent
of household income. With regard to state–level increase in unemployment rates, we
find that over the sample period, a 0.92 percentage point increase in the unemployment
rate leads to a reduction in SWB equivalent to a loss of $379 in monthly household
income, corresponding to 5.15 percent of household income. These estimates suggest
that wellbeing losses due to an increase in petrol prices are as important as wellbeing
losses created by weakening labour market conditions in the local economy.
Table 4.6 The income equivalence of rising petrol prices
Results in Australian
dollars per litre
Increase in petrol prices ($0.1547)
Monthly income equivalence
Yearly income equivalence
Percent of average household income
$538
$6,455
7.3%
Results in USD
based on increase
per gallon
US $0.4496
US $1,536
US $18,758
27.6%
Increase in unemployment (0.92 ppts)
Monthly income equivalence
Yearly income equivalence
Percent of average household income
$379
$4,550
5.15%
US $1,102
US $13,222
19.5%
Notes: The income equivalence for petrol price is based on a $0.1547 per litre increase in prices (the
standard deviation during the analysis period). To produce the calculations in the table, we first ran
regressions comparable to those in column (7) of Table 4.2, removing the petrol price variable and
replacing it with total monthly real household income and income squared. We then calculated the
change in life satisfaction due to a $1.00 increase in household income from the median (i.e., the
marginal effect). The median monthly household income for the overall sample is $6,487. The marginal
effects for monthly household income were then compared to the marginal effects for the petrol price
for the overall model. For example, to produce the monthly income equivalent of a $0.1547 per litre
increase in petrol prices, the following was calculated: $0.1547 x (-0.1095/ 0.0000315) = $538. The
same set of procedures were followed to obtain the income equivalence for state–level unemployment
rates. The average US:AUD exchange rate over 2001—2017 (1US:AUD1.3026) is used to covert
amounts in Australian dollars to US dollars.
How do these results compare with those in Boyd-Swan and Herbst (2012) who
perform a similar income equivalence exercise in the context of the United States? To
compare with Boyd-Swan and Herbst (2012) we use the average Australian-US dollar
exchange rate over the period 2001 to 2017 and convert our estimates from litres to
gallons. The results from doing this are also reported in Table 4.6. Our estimates per
litre are similar to Boyd-Swan and Herbst’s (2012) estimates per gallon. When we
129
convert from litres to gallons, the income equivalence of petrol price rises in our study
are considerably higher than in Boyd-Swan and Herbst (2012).
4.5.4.4 Employing alternative IVs
We use Dated Brent crude oil prices as an alternative instrument in Panel A of Table
4.7. The first stage result suggests that the crude oil price is positively correlated with
petrol price. The F-statistics (>10) and R-squared from the first stage regression,
indicates that the instrument is relevant. A one standard deviation increase in petrol
prices is associated with a 0.0234 standard deviation decrease in SWB in the 2SLS
estimates and a 0.0157 standard deviation decrease in SWB in the panel FE-IV
estimates. The estimates using this alternative IV are similar to those produced using
the NYSE Arca Oil Stock price index as the IV.
We next adopt the Lewbel (2012) approach which uses the presence of
heteroskedasticity as a precondition for identification to construct internally generated
instruments based on a heteroskedastic covariance restriction. Panel B reports findings
from Lewbel 2SLS regressions that use internally generated instruments only while
Panel C reports results for Lewbel 2SLS estimates that combine internally generated
instruments with our main external instrument (the NYSE Arca Oil Stock prices). The
heteroskedasticity assumption for Lewbel (2012) is fulfilled as the Breusch and Pagan
test for heteroskedasticity is significant indicating presence of heteroskedasticity. All
other tests for relevance and validity of the instruments are satisfied.
The estimates based on the Lewbel (2012) approach are higher than our baseline
estimates which lends support to our earlier claims that endogeneity generates
downward bias in our baseline estimates. However, these estimates are slightly lower
than those obtained using external instruments. Specifically, we find that a one
standard deviation increase in petrol prices lead to 0.0159 standard deviation decline
in SWB in panel B while in panel C, a one standard deviation increase in petrol prices
is associated with a decline of 0.0165 standard deviations in SWB. Each of the results
in Table 4.7 using alternative instruments support our conclusion that petrol price
increases have an adverse effect on SWB.
130
Table 4.7
Robustness checks: employing alternative IVs
Dependent variable (life satisfaction as a proxy for subjective wellbeing)
Variables
Panel A: IV is Dated Brent crude oil price
Petrol price
Observations
First stage
Instrument: Brent crude oil price
2SLS
Panel FE-IV
-0.2218***
(0.0564)
[-0.0234]
118,342
-0.1566***
(0.0506)
[-0.0157]
118,342
0.0136***
0.0136***
(0.0000)
(0.0000)
R-squared
0.6290
0.6290
F-Statistics
>10
>10
Panel B: IV (Lewbel internal generated instruments)
Petrol price
-0.1509***
(0.0540)
[-0.0159]
Observations
118,342
First stage
R-squared
0.7876
F-Statistics
>10
Panel C: Using Lewbel internal generated and external (NYSE Arca oil index)
IVs
Petrol price
-0.1568***
(0.0537)
[-0.0165]
Observations
118,342
First stage
Instrument: NYSE Arca Oil Stock
0.0001***
prices index
(0.0000)
R-squared
0.7931
F-Statistics
>10
Notes: All models include demographic and state-level controls and includes fixed effects at city,
monthly and yearly levels. For other notes see Table 4.2.
4.5.4.5 Alternative measures of wellbeing
As a further robustness check on our results, we use alternative ways of viewing and
measuring SWB in Table 4.8. In panel A, we treat SWB as ordinal and estimate
equation (4.1) using an ordered logit model. The estimates are consistent with our
baseline results.
In panel B, we follow the approach in Welsch and Biermann (2017) and measure life
satisfaction as a dummy variable in which we code the responses of participants that
report life satisfaction scores of 6—10 as ‘satisfied’ denoted by 1 and scores between
131
0 and 5 as ‘not satisfied’, denoted by 0. In panel C, instead of treating the mid-point as
the cut-off, for the purposes of constructing the dummy variable we treat those who
report life satisfaction above the mean value of 7.829 as ‘satisfied’ and below the mean
as ‘not satisfied’ in panel C. The results in panels B and C estimated using a logit
model are consistent with our baseline results.
Second, as an alternative, we use a measure of mental health to measure SWB. The
HILDA survey collects annual data on the SF-36 general health survey, which is used
to create the five-item Mental Health Inventory (MHI-5) scale. MHI-5 scale is a
measure of mental health intended to capture mood and emotion on a 0—100 scale.
The scale is based on the following items in which respondents were asked about how
often in the past four weeks they have: 1) been nervous; 2) felt so down in the dumps,
such that nothing could cheer them up; 3) felt calm and peaceful; 4) felt down; and 5)
been happy. Since it is hypothesised that rising petrol prices may cause a reduction in
happiness enhacing leisure travel activities, along with anxiety and stress due to the
perceived associated deterioration in the macroeconomic state of the economy, higher
petrol prices are likely to be associated with increased psychological distress. While
life satisfaction provides a cognitive appraisal of overall wellbeing and the MHI-5 is
designed to capture affective reactions to life circumstances, employing HILDA data
Wooden and Li (2014) show that the two are quite strongly correlated. Panel D of
Table 4.8 reports results for the association between petrol price and the MHI-5 scale.
We find that there is a significant negative relationship between petrol prices and
mental health, suggesting that rising petrol prices are associated with increased
psychological distress.
As an alternative to the MHI-5 scale, we use the Kessler Psychological Distress Scale
(K10) score and K10 score risk categories to measure psychological health. The K10
is based on a 10-item response measuring psychological distress, based on questions
about peoples’s level of nervousness, agitation, psychological fatigue and depression
in the past four weeks. By way of construction, lower scores indicate low levels of
psychological distress and high scores indicate high levels of psychological distress.
In panels E and F, we find that there is a significant positive association between petrol
prices and these alternative ways of constructing the K10 scale, reinforcing the
132
Table 4.8 Robustness checks: alternative measures of wellbeing
Variables
Panel A (Ordered Logit): Ordinal treatment of dependent variable
-0.1569***
(0.0462)
[-0.0165]
Observations
118,342
Panel B (Logit): DV is Life Satisfaction Dummy Using Welsch and Biermann
cut-offs
Petrol price
-0.2206**
(0.1024)
[-0.1343]
Observations
118,342
Panel C (Logit): DV is Life Satisfaction Dummy Using Mean Value as cut-off
point
Petrol price
-0.1945***
(0.0560)
[-0.0636]
Observations
118,342
Panel D (Panel FE-IV): DV is (MHI-5 Mental Health Scale)
Petrol price
Petrol price
Observations
Panel E (Panel FE-IV): DV is K10 Distress Scale score
-2.8713*
(1.7238)
[-0.0246]
105,696
1.1702**
(0.4872)
[0.0260]
Observations
39,906
Panel F (Panel FE-IV): DV is K10 Distress Scale score risk categories
Petrol price
0.1611*
(0.0864)
[0.0237]
39,906
Petrol price
Observations
Notes: All models include demographic and state-level controls and include fixed effects at city,
monthly and yearly levels. Individual fixed effects are also controlled for in Panel D, E and F. All
models are 2SLS, employing the NYSE Arca Oil Stock prices index as the IV. For other notes see Table
4.2.
conclusion from the MHI-5 scale findings in panel D that rising petrol prices are
associated with increased psychological distress.
133
The checks using K10 are based on waves 7, 9, 11, 13, 15 and 17 of the HILDA survey.
For completeness, instead of using K10, we re-estimated the FE-IV model for SWB,
restricting the sample to waves 7, 9, 11, 13, 15 and 17. When we do this, the coefficient
on SWB is positive, and significant. Alternatively, we also re-estimated the FE-IV
model for SWB, restricting the sample to all even years (2002, 2004, 2006, 2008, 2010,
2012, 2014 and 2016) and all odd years (2001, 2003, 2005, 2007, 2009, 2011, 2013,
2015 and 2017). In both cases, the coefficient on SWB was positive and statistically
significant, consistent with the results in Table 4.8. Results from this exercise are
presented in appendix Table A4.4.
4.5.4.6 Robustness to alternative fuel data and other sensitivity checks
Next, we examine the robustness of our findings to employing alternative fuel price
datasets. In Table 4.9, instead of monthly city—level unleaded petrol prices, we use
monthly city—level diesel prices. We adopt the same approach as in Table 4.3, where
we use the NYSE Arca Oil Stock prices as the instrument and progressively add more
controls to the 2SLS and panel FE-IV estimates. Our preferred POLS estimate in
column 7 suggests that a one standard deviation increase in diesel prices leads to a
0.0291 standard deviation decline in SWB, while the panel fixed effects estimates in
column 8 suggests that a one standard deviation increase in diesel prices lead to a
reduction in SWB by 0.0191 standard deviations.
We next examine if our results remain robust when we consider all participants in
HILDA, not just those who live in the cities. To do so, we use state—level data. At the
state-level, the only petrol price data is average annual petrol prices, which is available
from the Australian Institute of Petroleum website for 2002—2017. Because we are
considering all participants, and not just those who live in the cities, our sample size
is increased to 25,197 individuals with 217,654 observations who participated in at
least two waves of the survey. We match the state–level petrol price data to the annual
SWB scores of these participants. Results are presented in Table A4.5. The state—
level baseline, 2SLS and panel FE-IV estimates suggest a significant negative
association between petrol prices and SWB, consistent with our main results.
To complement the analysis in Table A4.5, we examine the impact of petrol prices on
SWB of those living in urban and rural areas based on vehicle ownership. These
134
Table 4.9
Robustness check: Petrol prices and subjective wellbeing using city-level monthly diesel price data (IV results)
Variables
Diesel price
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R-squared
Number of Individuals
First stage
Instrument:
NYSE Arca Oil Stock prices index
R-squared
F-Statistics
Notes: See notes to Table 4.2.
(1)
2SLS
(2)
Panel FE-IV
(3)
2SLS
(4)
Panel FE-IV
(5)
2SLS
(6)
Panel FE-IV
(7)
2SLS
(8)
Panel FE-IV
-0.2973***
(0.0437)
[-0.0393]
Yes
No
No
No
No
118,342
0.0827
-0.1127***
(0.0369)
[-0.0083)]
Yes
No
No
No
No
118,342
0.0135
14,953
-0.2913***
(0.0408)
[-0.0386]
Yes
Yes
No
No
No
118,342
0.0829
-0.1030***
(0.0330)
[-0.0085]
Yes
Yes
No
No
No
118,342
0.0136
14,953
-0.1856***
(0.0314)
[-0.0246]
Yes
Yes
Yes
No
No
118,342
0.0839
-0.0930***
(0.0277)
[-0.0087]
Yes
Yes
Yes
No
No
118,342
0.0137
14,953
-0.2201***
(0.0584)
[-0.0291]
Yes
Yes
Yes
Yes
Yes
118,342
0.0844
-0.1479***
(0.0488)
[-0.0191]
Yes
Yes
Yes
Yes
Yes
118,342
0.0143
14,953
0.0004***
(0.0000)
0.3100
>10
0.0004***
(0.0000)
0.3100
>10
0.0004***
(0.0000)
0.3720
>10
0.0004***
(0.0000)
0.3720
>10
0.0005***
(0.0000)
0.4822
>10
0.0005***
(0.0000)
0.4822
>10
0.0005***
(0.0000)
0.6402
>10
0.0005***
(0.0000)
0.6402
>10
135
results, which are presented in Table A4.6, suggest that for those who own a vehicle,
petrol price increases have a significant adverse effect on their SWB, but for who do
not own a vehicle, the effect of petrol price increases on SWB are insignificant. More
specifically, for a one deviation increase in petrol prices, those who own a vehicle in
rural areas experience a 0.0276 standard deviation decline in SWB, while those who
own a vehicle in urban areas experience a smaller 0.0151 standard deviation decline
in SWB. These results reflect that people living in rural areas are more reliant on their
vehicles to travel for work and leisure, given that rural areas are sparsely populated
with often long distances between towns that have few, or no, public transport options.
Our results are consistent with Dodsen and Sipe (2007) who argue that car dependence
in rural areas in Australia makes people vulnerable to increased fuel costs as they
heavily rely on cheap petrol prices. However, those in city and inner suburban areas
with much easier access to public transportation system will be less disadvantaged by
higher petrol prices.
In Table A4.7 we consider if our main results are robust to using a range of alternative
fuel price datasets at different frequencies and for geographical areas. In panel A and
panel B, we use annual data obtained at the city–level from the Australian Institute of
Petroleum website for petrol and diesel for the period 2004—2017, respectively. The
estimates in both panels suggest a negative association between both petrol and diesel
prices and SWB. In panel C, we match state—level diesel price data from the
Australian Institute of Petroleum website to the annual SWB scores of participants
over the 2004—2017 period and find a negative relationship. Finally, we match petrol
and diesel price data from the Western Australia Fuel Watch website for Western
Australian regions with SWB data for Western Australian participants in HILDA for
the period 2001-2017. The relationship between petrol prices and SWB are again
negative.
Our baseline estimates in Table 4.2 are estimated with cluster-robust standard errors
at the individual level. As a check, we re-estimated the baseline results with a full set
of controls (Column 8 of Table 4.2), clustering the standard errors at the city-level. We
find that the results, which are presented in appendix Table A4.8, are robust to
clustering at the city-level.
136
While some studies use disposable income in SWB regressions (see for e.g. Anwar,
Astell-Burt & Feng, 2019; Bernardelli, Kortt & Michellon, 2019; Johnston, Shields &
Suziedelyte, 2018; Lorenz, 2018), others use equivalized income (see for e.g. Aitken,
Simpson, Gurrin, Bentley & Kavanagh, 2018; Huang, Frijters, Dalziel & Clarke, 2018;
Kristoffersen, 2018; Wooden & Li, 2014). In our main results, we present estimates
for regressions that control for the log of real household disposable total income
measured in dollars. In Table A4.9, we examine the sensitivity of our results to the
use of equivalized income,28 and thus we used equivalized income instead of
disposable income and the results are qualitatively the same.
In our main results, we include year and month fixed effects, but one might be
concerned that there are seasonal variations that influence changes in SWB and petrol
prices which may not be captured with time fixed effects. In particular, as a result in
climate change, hotter weather may decrease SWB but increase petrol prices. This
would be consistent with the heterogeneity analysis presented in Figure 4.2. To
examine this issue, we included average monthly temperature in the full model
specification in the baseline and IV results. The results are reported in Table A4.10.
The coefficient on petrol prices continues to be negative and significant with very
similar magnitudes to columns 7 and 8 in Table 4.2 and Table 4.3. The coefficient on
‘temperature’ is insignificant in the 2SLS and Panel FE-IV specifications.
4.6
Conclusion
We have examined the relationship between petrol prices and SWB for Australia using
the nationally representative longitudinal HILDA dataset over the period 2001—2017.
We find that there is a significant negative association between petrol prices and SWB.
This finding is robust to a number of checks for endogeneity, employing alternative
ways of defining wellbeing and the use of a range of alternative datasets covering
different geographical areas and measures of fuel prices at alternative frequencies. We
also examine the role of consumption choices and maintaining social networks as
channels through which petrol prices affect SWB and find that maintaining contact
with family and friends are important channels.
28
Equivalized household income is calculated using the formula: household disposable total income /
[1 (first adult in the household) + 0.5 * (second and each subsequent person aged 14 and over in the
household) + 0.3 * (each child aged under 14 in the household)].
137
Our results suggest that rising petrol prices have direct significant adverse effects on
the benefits realized via travel. This is particularly important in Australia given that
many people are reliant on cars for travel and poor public transport options in many
Australian cities, particularly in the outer suburbs of major metropolitan areas in which
most people live, mean that there are few realistic alternatives to travelling by car when
petrol prices rise. Overall, 80 percent of urban passenger travel is via cars, with a little
more than 10 percent done by mass transit (Bureau of Infrastructure, Transport and
Regional Economics, 2016). The increased availability, and affordability, of cars in
Australia has brought with it benefits such as the ability to obtain employment further
afield, take longer trips to see family and friends and engage in cultural and social
activities (Australia Bureau of Statistics, 2013); however, our estimates suggest that
increases in petrol prices limits engagement in these happiness-enhancing activities,
thereby having an adverse effect on the individual life satisfaction.
Given that we find adverse effects of both diesel and petrol prices, as well as their
volatility, on the wellbeing of individuals, an important policy implication of our
finding is to subsidise alternatives to fuel cars, such as electric cars.29 Increased
prevalence of electric cars would not only reduce the susceptibility of people’s SWB
to movements in fuel prices, but also be more environmentally friendly, which is
relevant as Australia is a signatory of the Paris agreement to achieve net zero carbon
emissions by 2050. In Australia, there are currently very limited incentives for
individuals to switch to electric vehicles. In one recent news report, Chang (2019)
documents that electric vehicles represent just 0.2 percent of automobiles in the
country. However, research by Australian Automotive Aftermarket Association
(2019) finds that about 54 percent of Australians would be likely to buy an electric
vehicle if given attractive government incentives, such as tax credits and discounts on
vehicle fees. Our results also support Currie, Delbosc and Pavkova’s (2018) call for
greater investment in public transport services in Australia, especially in outer
suburban areas, together with policies to promote safe cycling and walking
29
This suggestion relies on the assumption that dependence on electricity prices is better than
dependence on petrol prices, which, in turn, relies on the assumption that electricity is produced with
low carbon emitting technologies.
138
infrastructure. Improved public transport options would provide alternatives to travel
by car and reduce the sensitivity of SWB to petrol prices.
139
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APPENDICES
Table A4.1
Description and Summary Statistics of variables
Variables
Subjective
wellbeing
(life satisfaction)
Petrol prices
Age
Age squared
Male
Female
Dependants
Separated
Divorced
Widowed
Single
Income
Employed
Unemployed
Postgraduate
Graduate
Diploma
Bachelor
Diploma
Certificate
Year 12
Descriptions
How satisfied are you with your life? On a
scale of 0—10, where 0 is labelled as totally
dissatisfied and 10 is totally satisfied
Real ULP prices measured in Australian
dollars per litre
Age of the survey respondents measured in
years.
Square of age/100
Dummy variable if respondent is male
Dummy variable if respondent is female
Number of dependents in household aged
0—24
Dummy variable if respondent is separated
Dummy variable if respondent is divorced
Dummy variable if respondent is widowed
Dummy variable if respondent is single
Log of real household disposable total
income measured in dollars
Dummy variable if respondent is employed
Dummy variable if respondent is
unemployed or not in labour force
Dummy variable if respondent’s highest
education level achieved is masters or
doctorate
Dummy variable if respondent’s highest
education level achieved is graduate
diploma or certificate
Dummy variable if respondent’s highest
education level achieved is bachelor or
honors
Dummy variable if respondent’s highest
education level achieved is advanced
diploma or diploma
Dummy variable if respondent’s highest
education level achieved is certificate I, II,
III or IV
Dummy variable if respondent’s highest
education level achieved is year 12 or below
150
Mean
7.8287
SD
1.4681
1.2987
0.1547
44.9931
17.7427
23.3918
0.4683
0.5317
0.6375
17.6631
0.4990
0.4990
1.0467
0.0261
0.0647
0.0488
0.2180
11.0945
0.1593
0.2460
0.2155
0.4129
0.7866
0.6711
0.3289
0.4698
0.4698
0.0623
0.2417
0.0643
0.2452
0.1782
0.3827
0.0970
0.2959
0.1842
0.3877
0.4141
0.4926
Illness
0.2231
0.4163
10.0161
9.5667
Log of real gross state domestic product per
capita measured in thousands
4.1892
0.1351
Five-item Mental Health Inventory (MHI-5)
scale
Kessler Psychological Distress Scale (K10)
73.8619
17.0829
15.8724
6.3905
Kessler Psychological Distress Scale (K10)
risk categories. 1 represents low risk, 2
moderate risk, 3 high risk and 4 very high
risk
Diesel prices
Real diesel prices measured in Australian
dollars per litre
Community
In general, how often do you see members
participation: See of your extended family (or relatives not
members of
living with you) in person? On a scale of
extended family 1—6, where 1 is labelled as never’ and 6 is
‘very often’
Community
In general, how often do you make time to
participation:
keep in touch with friends? On a scale of
Keep in touch
1—6, where 1 is labelled as ‘never’ and 6 is
with friends
‘very often’
Household
Log of household expenditure on meals
expenditure on
eaten out measured in dollars
meals eaten out
City
City is defined by area postcodes that are in
the seven major metropolitan areas in
Australia: Adelaide (5000—5199), Brisbane
(4000—4207, 4300—4305, 4500—4519),
Darwin (800-832), Hobart (7000—7004),
Melbourne (3000—3207), Perth (6000—
6109), Sydney (2000—2234). Numbers in
parenthesis are Australian area postcodes
State
8 states in Australia: New South Wales,
Victoria, Queensland, South Australia,
Western Australia, Tasmania, Northern
Territory, Australian Capital Territory.
1.5791
0.8753
1.3580
0.1943
3.9518
1.3024
4.4512
1.0832
5.3528
0.7962
Population
density by state
Gross state
product per
capita
Mental health
K10 Distress
Scale
K10 Risk
Categories
Dummy variable if respondent is disabled or
has a long-term illness
Persons per square kilometer by state
151
Table A4.2
Test on the validity of IV
Variables
Dependent variable: Maximum monthly
temperature
NYSE Arca Oil Stock prices index
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R-squared
Number of Individuals
Pooled OLS
Panel FE
0.0000
(0.0001)
[0.0018]
Yes
Yes
Yes
Yes
Yes
118,342
0.8516
0.0000
(0.0000)
[0.0002]
Yes
Yes
Yes
Yes
Yes
118,342
0.6584
14,953
Notes: The maximum monthly temperature data is sourced from The Bureau of Meteorology - Australia
website (http://www.bom.gov.au/climate/data/index.shtml). Daily maximum temperature is obtained
from various existing weather stations to calculate monthly average maximum temperature by city. For
other notes see Table 4.2
152
Table A4.3 Petrol prices and Life satisfaction, full baseline and 2SLS results
Variables
Petrol price
Female
Age
Age squared
Dependants
Separated
Divorced
Widowed
Single
Income
Employed
Postgrad
Graduate Diploma
Baseline
Pooled OLS
Panel FE
-0.1092***
(0.03650)
[-0.0115]
0.1141***
(0.0202)
[0.0388]
-0.0586***
(0.0034)
[-0.7082]
0.0720***
(0.0036)
[0.8661]
-0.0492***
(0.0093)
[-0.0351]
-0.8526***
(0.0570)
[-0.0925]
-0.4584***
(0.0467)
[-0.0768]
-0.2930***
(0.0537)
[-0.0430]
-0.3679***
(0.0268)
[-0.1035]
0.1803***
(0.0123)
[0.0966]
0.1064***
(0.0225)
[0.0341]
-0.0830**
(0.0397)
[-0.0137]
-0.0534
(0.0404)
[-0.0089]
-0.1137***
(0.0414)
[-0.0120]
-0.0144***
(0.0049)
[-0.1744]
0.0121***
(0.0043)
[0.1457]
-0.0583***
(0.0092)
[-0.0416]
-0.6417***
(0.0464)
[-0.0696]
-0.3705***
(0.0466)
[-0.0621]
-0.4196***
(0.0642)
[-0.0616]
-0.2592***
(0.0230)
[-0.0729]
0.0392***
(0.0093)
[0.0210]
0.0508***
(0.0164)
[0.0163]
-0.0360
(0.0504)
[-0.0059]
-0.1002**
(0.0499)
[-0.0167]
153
2SLS
Pooled OLS Panel FE
-0.2324***
(0.0617)
[-0.0245]
0.1143***
(0.0202)
[0.0389]
-0.0588***
(0.0034)
[-0.7102]
0.0722***
(0.0036)
[0.8686]
-0.0493***
(0.0093)
[-0.0352]
-0.8511***
(0.0571)
[-0.0924]
-0.4567***
(0.0467)
[-0.0765]
-0.2919***
(0.0537)
[-0.0428]
-0.3667***
(0.0268)
[-0.1031]
0.1840***
(0.0125)
[0.0986]
0.1055***
(0.0225)
[0.0338]
-0.0820**
(0.0396)
[-0.0135]
-0.0529
(0.0404)
[-0.0088]
-0.1566***
(0.0517)
[-0.0157]
-0.0158***
(0.0050)
[-0.1905]
0.0122***
(0.0043)
[0.1474]
-0.0585***
(0.0092)
[-0.0417]
-0.6418***
(0.0464)
[-0.0697]
-0.3702***
(0.0466)
[-0.0620]
-0.4189***
(0.0642)
[-0.0615]
-0.2591***
(0.0230)
[-0.0729]
0.0398***
(0.0093)
[0.0213]
0.0508***
(0.0164)
[0.0163]
-0.0364
(0.0505)
[-0.0060]
-0.1003**
(0.0499)
[-0.0167]
Bachelor
Diploma
Certificate
Long–term illness
Population Density
Gross state product per
capita
City FE
Monthly FE
Year FE
Observations
R–squared
Number of Individuals
-0.0855***
(0.0270)
[-0.0223]
-0.0195
(0.0336)
[-0.0039]
-0.0240
(0.0275)
[-0.0063]
-0.6009***
(0.0221)
[-0.1704]
-0.0017
(0.0075)
[-0.0110]
0.2804*
(0.1508)
[0.0258]
Yes
Yes
Yes
118,342
0.0842
-0.1375***
(0.0317)
[-0.0359]
-0.0944*
(0.0492)
[-0.0190]
-0.0681*
(0.0356)
[-0.0180]
-0.1959***
(0.0130)
[-0.0555]
-0.0180**
(0.0070)
[-0.1172]
-0.0130
(0.1758)
[-0.0012]
Yes
Yes
Yes
118,342
0.0142
14,953
-0.0849***
(0.0270)
[-0.0221]
-0.0192
(0.0336)
[-0.0039]
-0.0227
(0.0275)
[-0.0060]
-0.6008***
(0.0221)
[-0.1704]
-0.0032
(0.0075)
[-0.0206]
-0.0830
(0.1977)
[-0.0076]
Yes
Yes
Yes
118,342
0.0844
-0.1377***
(0.0317)
[-0.0359]
-0.0947*
(0.0492)
[-0.0191]
-0.0681*
(0.0356)
[-0.0180]
-0.1959***
(0.0130)
[-0.0555]
-0.0186***
(0.0070)
[-0.1215]
-0.0176
(0.1758)
[-0.0016]
Yes
Yes
Yes
118,342
0.0143
14,953
Notes: See notes to Table 4.2. Reference category for marital status are those married or in a de facto
relationship, for educational status it is those whose highest education level is year 12 or below, and
for employment status it is those unemployed or not in the labour force.
154
Table A4.4
Petrol prices and subjective wellbeing, alternating years
(2)
Variables
Panel FE-IV
Panel A: restricting SWB sample over same years as K10 variable
Petrol price
-0.1914*
(0.1050)
[-0.0152]
Observations
45,198
Panel B: restricting SWB sample to odd years of the survey
Petrol price
-0.2133***
(0.0653)
[-0.0190]
Observations
63,221
Panel C: restricting SWB sample to even years of the survey
Petrol price
-0.0968*
(0.0572)
[-0.0091]
Observations
55,121
Notes: All models include demographic and state-level controls and includes fixed effects at state and
yearly levels. For other notes see Table 4.2.
155
Table A4.5 Petrol prices and subjective wellbeing, using state-level yearly petrol
prices
Variables
Panel A: Baseline Results
Petrol price
Observations
R-squared
Number of Individuals
Panel B: IV Results
Petrol price
Observations
Number of Individuals
First stage
Instrument:
NYSE Arca Oil Stock prices
index
R-squared
F-Statistics
(1)
Pooled OLS
(2)
Panel FE
-0.1154***
(0.0307)
[-0.0109]
217,654
0.0792
-0.2592***
(0.0413)
[-0.0244]
217,654
0.0137
25,197
2SLS
-0.3789***
(0.0568)
[-0.0357]
217,654
Panel FE-IV
-0.1638***
(0.0286)
[-0.0147]
217,654
25,197
0.0004***
(0.0000)
0.0004***
(0.0000)
0.5183
>10
0.5183
>10
Notes: All models include demographic and state-level controls and includes fixed effects at state and
yearly levels. The data for state level petrol price is for the period 2002 —2017. For other notes see
Table 4.2.
156
Table A4.6 Petrol prices and subjective wellbeing, heterogeneous effects by
geographical location and vehicle ownership using state-level yearly
petrol prices
Panel A: Urban
Variables
Petrol price
Observations
Panel B: Rural
Variables
Petrol price
Observations
Own a vehicle
Panel FE-IV
-0.1664**
(0.0791)
[-0.0151]
119,002
Do not own a vehicle
Panel FE-IV
-0.3247
(0.2118)
[-0.0227]
33,788
Own a vehicle
Panel FE-IV
-0.3004**
(0.1474)
[-0.0276]
14,390
Do not own a vehicle
Panel FE-IV
-0.4465
(0.5090)
[-0.0306]
3,341
Notes: All models include demographic and state-level controls and includes fixed effects at state and
yearly levels. The NYSE Arca Oil Stock prices index is used as instrument in all the specifications. For
other notes see Table 4.2.
157
Table A4.7
Petrol prices and subjective wellbeing using alternative yearly fuel
prices (IV results)
Variables
Panel A: City-level yearly ULP prices
Petrol price
2SLS
Panel FE-IV
-0.3385***
(0.0773)
[-0.0326]
100,138
-0.1901***
(0.0482)
[-0.0172]
100,138
-0.3222***
(0.0736)
[-0.0401]
100,138
-0.1670***
(0.0429)
[-0.0197]
100,138
-1.6267**
(0.8111)
[-0.2059]
Observations
159,697
Panel D: Western Australia – yearly ULP prices
Petrol price
-0.4158***
(0.1522)
[-0.0372]
Observations
21,733
Panel E: Western Australia – yearly Diesel prices
Diesel prices
-0.2686***
(0.0983)
[-0.0299]
Observations
21,733
-0.0901*
(0.0481)
[-0.0114]
159,697
Observations
Panel B: City-level yearly Diesel prices
Diesel price
Observations
Panel C: State-level yearly Diesel prices
Diesel price
-0.2065*
(0.1150)
[-0.0184]
21,733
-0.1842*
(0.1017)
[-0.0205]
21,733
Notes: All models include demographic and state-level controls and includes fixed effects at
state/city/region and yearly levels. In Panel A and B, the data for city level petrol and diesel price is
sourced from Australian Institute of Petroleum website for the period 2004 —2017. In Panel C, the data
for state level diesel price is sourced from Australian Institute of Petroleum website for the period
2007—2017. In Panel D and E, the data for petrol and diesel price for Western Australia regions is
sourced from Western Australia Fuel Watch website for the period 2001—2017. The NYSE Arca Oil
Stock prices index is used as the instrument in all specifications. For other notes see Table 4.2.
158
Table A4.8 Petrol prices and subjective wellbeing, clustering at city-level
Variables
Petrol price
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R-squared
Number of Individuals
Panel FE
-0.0486***
(0.0120)
[-0.0051]
Yes
Yes
Yes
Yes
Yes
118,342
0.5791
14,953
Notes: See notes to Table 4.2.
159
Table A4.9 Petrol prices and subjective wellbeing, using equivalized income
Variables
Petrol price
Equivalized Income
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R–squared
Number of Individuals
Baseline
Pooled OLS
Panel FE
-0.1113***
(0.0366)
[-0.0117]
0.2077***
(0.0142)
[0.0944]
Yes
Yes
Yes
Yes
Yes
118,314
0.0841
-0.1134***
(0.0519)
[-0.0119]
0.0474***
(0.0105)
[0.0215]
Yes
Yes
Yes
Yes
Yes
118,314
0.0142
14,950
Notes: See notes to Table 4.2.
160
2SLS
Pooled OLS Panel FE
-0.2390***
(-0.0617)
[-0.0252]
0.2129***
(0.0145)
[0.0967]
Yes
Yes
Yes
Yes
Yes
118,314
0.0842
-0.1573***
(-0.0517)
[-0.0158]
0.0482***
(0.0105)
[0.0219]
Yes
Yes
Yes
Yes
Yes
118,314
0.0144
14,950
Table A4.10 Baseline and 2SLS results, using average monthly temperature as
an additional control variable
Variables
Petrol price
Temperature
Demographic controls
State-level controls
City FE
Monthly FE
Yearly FE
Observations
R–squared
Number of Individuals
Baseline
Pooled OLS
Panel FE
2SLS
Pooled OLS Panel FE
-0.0863***
(0.0386)
[-0.0091]
-0.0047**
(0.0024)
[-0.0135]
Yes
Yes
Yes
Yes
Yes
118,342
0.0843
-0.2339***
(0.0616)
(-0.0247)]
-0.0033
(0.0024)
[-0.0093]
Yes
Yes
Yes
Yes
Yes
118,342
0.0842
-0.1101***
(0.0414)
[-0.0065]
-0.0034*
(0.0020)
[-0.0096]
Yes
Yes
Yes
Yes
Yes
118,342
0.0142
14,953
-0.1600***
(0.0521)
(-0.0160]
-0.0029
(0.0020)
[-0.0083]
Yes
Yes
Yes
Yes
Yes
118,342
0.0143
14,953
Notes: Temperature is variable capturing average monthly temperature at the city level. For other
details, see notes to Table 4.2.
161
CHAPTER 5
CONCLUSION
162
There is now a rapidly growing literature in economics investigating what influences
wellbeing and the challenges that these empirical findings pose for policy. In the last
decade, the advancement in data gathering, advanced statistical techniques and
increased computing power has led to significant increases in the study of the
correlates with SWB. Despite the growing popularity of wellbeing measures in the
academic and policy debate, significant gaps remain in the literature. Advancing the
understanding on the dynamics and determinants of SWB was my focus in this
dissertation with three papers on SWB.
The first paper of this dissertation focussed on the effect of one of the important
objectives for many people in their life, that is to own one’s home. The focus in this
paper was on the effect of parental homeownership status on the SWB of children. In
presenting the first study to examine in depth the relationship between homeownership
and SWB of children, I find that parental homeownership status has a positive and
significant effect on the SWB of their children using longitudinal data from China.
Using different model specifications and addressing endogeneity of homeownership,
the welfare effects of homeownership on children remain robust. Given rising
homeownership rates in China, this finding suggests that government policies should
promote full homeownership with residential property rights over renting in order to
realize higher SWB of children. This result also calls for greater regulation of the real
estate market in urban China and policies to remove discrimination in the housing
market, to ensure that the benefits of homeownership are not illegally denied to
minority children. The findings are important for parents wanting to improve the SWB
of their children. They suggest that homeownership provides an important antecedent
to doing this.
Further results from the mediation analysis finds that parental inputs into their
children’s education, investment in home maintenance, the quality of the
neighbourhood and parents’ emotional support for their children are important
pathways that enhance the child’s SWB. This analysis suggests that government
policies to invest in improving the quality of neighbourhoods and to invest in betterquality non-owner-occupied housing might enhance these pathways that would bring
about similar positive effects to homeownership per se. While these findings are
informative, future research should expand on this work by examining the relationship
163
between homeownership and SWB of children in other countries, perhaps where
homeownership rates are lower. Other directions for future research include examining
various heterogenous effects of homeownership on SWB of children or examining the
relationship between homeownership and objective outcomes of children, such as
performance in school, for which there are few studies. There is also potential scope
in the future to explore the role of various different housing characteristics, such as
neighbourhood conditions, dwelling size, sanitation and internet connections as
moderators or mediators of the relationship between homeownership and child
outcomes. This would provide a richer framework for designing appropriately targeted
homeownership policies.
In the second paper of this thesis, I examined the issue of rising global wealth
inequality, inspired by the work of Piketty (2014). Given rising homeownership rates
in China, as discussed in the first paper, China represented an ideal case to study the
effects of rising housing wealth inequality on individual wellbeing. In presenting the
first in-depth study on how housing wealth and inequality in housing wealth is
associated with happiness, either for China or other countries, I find that housing
wealth is positively associated with happiness in urban China and that this is
particularly true for the in-group comparison and when city is the reference point. I
find that a general increase in housing wealth inequality at the province level lowers
happiness. I explain this result by arguing that there exists a jealousy effect as
individuals are unable to relate to those at the top end of the distribution and, hence,
feel unable to replicate their success. On the contrary, I find that an increase in housing
wealth inequality within a narrowly defined reference group – those of the same
gender, similar age and education living in the same city – up to a certain point
increases happiness. This represents a signalling effect, in which individuals feel
empowered by the success of others with very similar characteristics to them and, as a
result, feel that they are well placed to replicate their success. Nonetheless, beyond a
certain point this ceases to be the case because the success of those at the top end of
the distribution appears out of reach. In additional analysis, I also find that there are
diminishing returns to happiness from owning more than one house.
An important policy implication of findings from the second paper is that the
government should take steps to reduce general inequality in housing wealth and to
164
create more opportunities for those without housing wealth to build at least modest
levels of housing wealth. I suggest, in the context of Chinese economy, that this can
be done by the government taking steps to subsidise low-income housing and possibly
by introducing economy wide fixed asset taxes to curb housing wealth at the top of the
distribution. These interventions have the potential to reduce housing wealth inequality
in order to make happy communities.
In the third paper of this dissertation, I examined the effect of petrol prices and its
volatility on individual SWB. Using the HILDA dataset for Australia, I find that there
is significant adverse effects of petrol prices and its volatility on individual SWB.
These findings remained robust to a number of checks for endogeneity, employing
alternative definitions of wellbeing and to the use of alternative datasets and fuel prices
at alternative frequencies.
Mediation analysis showed that maintaining social networks is an important channel
through which petrol prices affect SWB. Given Australia’s heavy reliance on cars for
travel, the findings from this paper has important policy implications. To mitigate the
negative consequences of petrol prices on wellbeing, my results suggest the need for
increased government investment in public transport services, safe cycling, and
walking infrastructure and for subsidies to promote alternatives to fuel cars. With
improved options, these would provide alternatives to travel by car and reduce the
sensitivity of individual SWB to petrol prices.
Research into the dynamics and determinants of SWB is growing rapidly. Given the
increasing relevance of using wellbeing measures in public policy, there is increasing
interest in knowing which factors cause happiness and the channels through which this
occurs, along with ways to achieve optimal levels of happiness for individuals and
societies. This dissertation contributes to furthering efforts in understanding the
dynamics of SWB.
165