1113801
NVSXXX10.1177/08997640221113801Nonprofit and Voluntary Sector QuarterlyWang
research-article2022
Articles
What Matters for
Charitable Donations
Under Authoritarianism?
An Examination of
Organizational Legitimacy
and Political Connections
Nonprofit and Voluntary Sector Quarterly
1–30
© The Author(s) 2022
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https://doi.org/10.1177/08997640221113801
DOI: 10.1177/08997640221113801
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Qun Wang1
Abstract
Voluntary certification that signals nonprofit organizations’ legitimacy has been
found to be positively related to charitable donations in Europe and North
America. However, whether these proxies of organizational legitimacy matter under
authoritarian regimes where political connections are deemed critical for resource
acquisition has not been explored. Based on a sample of 2,021 Chinese foundations,
this article finds that organizational legitimacy achieved through certification is tied
to an increase in charitable donations. Meanwhile, organizational legitimacy tends to
negatively moderate the relationship between foundations’ political affiliation and
charitable donations. That is, certification lifts the amount of charitable donations
to civic foundations that are not formally affiliated with the state more than it does
for politically affiliated foundations. As the first quantitative study on the effect of
voluntary nonprofit certification programs on charitable donations outside Western
democracies, this article contributes to our understanding of fundraising in China and
other authoritarian states.
Keywords
organizational legitimacy, accreditation and certification, political connections,
charitable donations, authoritarianism
1
The University of Toledo, OH, USA
Corresponding Author:
Qun Wang, Department of Political Science and Public Administration, The University of Toledo, Snyder
Memorial Building 3007, MS 140, Toledo, OH 43606-3390, USA.
Email: qun.wang@utoledo.edu
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Nonprofit and Voluntary Sector Quarterly 00(0)
Introduction
Throughout the 1990s, articles about nonprofit wrongdoings began to permeate the
U.S. press. Gibelman and Gelman (2004) identified theft, mismanagement of resources,
excessive compensation, and so forth among U.S. nonprofits from media reports during the period 2001–2004. “The nonprofit sector’s claims to exist for the public good
are no longer being taken on faith” (Brody, 2002, p. 472). Now donors demand verification, because it is difficult to know whether a charity’s request for support is legitimate (Princeton Survey Research Associates, 2001). The United States is not an
isolated case. The press and academia have highlighted scandals of the nonprofit sector in various countries and requested proof for legitimacy.
In response, pursuance of accreditation and certification for organizational legitimacy among nonprofits, initiated by either watchdog or government agencies, has
been on the rise globally (Gugerty, 2009). Accreditation and certification are processes
of assessment by an external organization that investigates the operation of an applicant (N. C. Feng et al., 2019; Ortmann & Myslivecek, 2010). They typically involve a
review of organizations’ conformity, competence, and accountability against established standards. According to the signaling theory, nonprofits may utilize accreditation and certification to demonstrate their legitimacy (N. C. Feng et al., 2019). This
way they differentiate themselves and convince stakeholders they deserve resources.
Empirical research on nonprofits based in Europe and North America has supported a
positive relationship between organizational legitimacy attested through accreditation
and certification and donation income (e.g., Bekkers, 2003; N. C. Feng et al., 2019).
Nonprofits have grown rapidly outside Western democracies in the last few
decades. Realizing that a strong group of socially oriented organizations fundamentally align with regime interests, authoritarian states began to tolerate nongovernmental organizations (NGOs) independent of the state and incorporated
capacity-building into their nonprofit policy. Meanwhile, in countries such as Russia,
Turkey, and China, charitable donations have become a major source of nonprofit
revenue.1 However, little research has focused on organizational legitimacy symbolized through sector-wide nonprofit accreditation and certification (for an exception,
see Cheng & Wu, 2021).
Under authoritarian rule, political institutions function in the state-controlled
resource ecology. States are both governor and competitor in the nonprofit sector
(Kang, 2018). Because charitable donation is limited, governments must be selective
in their help and direct this source of revenue to key NGOs that serve as state agent and
social actor at the same time. Not surprisingly, the literature usually acknowledges the
environmental restrictions and investigates the impact of NGOs’ political connections
on nonprofit revenue (e.g., Johnson & Ni, 2015; Ni & Zhan, 2017; Wei, 2020; Zhao
et al., 2016). The rationale is that NGOs need to maintain strong and dependent relationships with the state for resources needed to advance their work.
The findings of political connections’ tie to nonprofit revenue, however, became
increasingly mixed. Wei (2020) suggested that in China NGOs’ political connections
play an indirect role. Therefore, political connections may affect fundraising
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3
contingently through their interactions with other organizational attributes. Using
2,021 foundations in China—which are 66.72% of the entire population of foundations registered before 2013—this study helps fill the gaps by examining how organizational legitimacy (i.e., certification), political connections, and their interactions are
related to charitable donations.
China was chosen as the empirical setting for several reasons. In the current century, the Chinese party-state has gradually reduced its long-term funding commitment
to NGOs, leaving many NGOs to rely on other sources of revenue. In comparison to
other authoritarian states, China has more available data and empirical studies.
Although China has its own peculiarities, distinct authoritarian regimes have exhibited
surprisingly similar patterns in their nonprofit policy (Richter & Hatch, 2013). As the
largest authoritarian state in the world, what is happening to Chinese NGOs is relevant
for nonprofit sectors outside Western democracies.
Findings from this study can directly inform prior literature and make three specific
contributions. First, it introduces voluntary accreditation and certification to the study
of nonprofit fundraising under authoritarianism. Prior studies used internal organizational variables not readily visible to potential donors, such as expertise, as legitimacy.
Recently, Cheng and Wu (2021) found that the level of transparency among Chinese
foundations, measured by the Foundation Transparency Index (FTI), was positively
tied to donation income. Different from Cheng and Wu, this current study examines
three certification programs that foundations voluntarily participate in rather than
being passively rated. It also differs in that Cheng and Wu emphasized accountability
through information disclosure, whereas this study focuses on regulatory conformity
and the adoption of best practices.
Second, by combining three data sources, this study creates a unique data set that
measures political connections through organizational affiliation with the state in addition to board interlocking. Prior research usually operationalized political affiliation
into a dichotomous variable so that an NGO was either politically affiliated or not
(e.g., Li et al., 2017). Jia (2011) argued that the differentiation of NGOs’ political
affiliation is hidden if we see Chinese NGOs this way. This study considers the nature,
formation, and degree of NGOs’ affiliation and categorizes it according to governmental and quasi-governmental affiliation. How the two forms of political affiliation are
tied to charitable donations may reveal nuances largely ignored in prior literature. This
novel operationalization of political affiliation can be a useful methodological tool for
future research.
Finally, this study connects the organizational legitimacy literature advanced in
Western societies and political determinants as propositions for authoritarian regimes
by examining the moderating effect of organizational legitimacy on the relationship
between political connections and charitable donations. Prior studies usually excluded
the potential moderating effect of organizational attributes on political connections
(e.g., Johnson & Ni, 2015) or considered the value of political connections as contingent on external shock (Ni & Zhan, 2017). In a rare exception, Cheng and Wu (2021)
found that in China the presence of government officials on boards of directors helped
foundations obtain more charitable donations only when foundations achieved roughly
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Nonprofit and Voluntary Sector Quarterly 00(0)
above 60% of the FTI scores. Alternatively, this study investigates whether the outcome of voluntary certification programs leverage the effect of both the number of
government officials and the political affiliation on charitable donations. To a certain
extent, this study contributes to the reconciliation of prior literature and a comprehensive understanding of government-NGO relations and fundraising under authoritarian
rule.
The rest of the article is structured as follows. First, it reviews the literature and
proposes hypotheses. Next, it describes the research context, data, variables, and
method. It then presents the results and discusses the implications. It concludes with a
summary and limitations of the study.
Literature Review
Organizational Legitimacy Through Accreditation and Certification
Organizational legitimacy is a generalized perception that the actions of an entity are
desirable, proper, or appropriate within a system of norms, values, and beliefs
(Suchman, 1995). Stakeholders perceive legitimate organizations as more trustworthy.
Therefore, nonprofits may adopt endorsed practices into their formal structure (Powell
& DiMaggio, 1991). Agency theory posits that to reduce risk, donors look for “insurance” that nonprofits allocate donated funds appropriately (Slatten et al., 2011). In a
robust civil society, resource providers tend to provide resources to an NGO that possesses perceived legitimacy (Galaskiewicz & Bielefeld, 1998).
NGOs are an emerging organizational field in most authoritarian societies. The
public does not understand NGO operations very well (Henderson, 2011; Hsu &
Hasmath, 2017). Moreover, donors encounter information asymmetry in the donation
process and lack the expertise to thoroughly evaluate each NGO (Parsons, 2007). This
is especially true where transparency is low in the nonprofit sector. In fact, low transparency has inhibited philanthropy in China and other transitioning countries
(Wiepking & Handy, 2015). Table 1 presents three indexes rating nonprofit transparency in China. Each index similarly inspected the disclosure of organizational, governance, financial, and program information and gave low scores. A survey by the China
Charity Information Centre reported that in 2013 about 80% of the people were unsatisfied with nonprofit transparency.2 Even in 2020, only 30% of the rated foundations
disclosed financial reports, and 14.6% had little information available to the public
(see Sources in Table 1).
Proxies of organizational legitimacy that are easier to perceive and access, such as
accreditation and certification, thus give donors useful references other than performance measures drawn from often hard-to-obtain NGO annual reports. Unlike their
passive role when rated by a watchdog agency, NGOs actively seek to be accredited or
certified for a score, status, or qualification (N. C. Feng et al., 2016). Accreditation and
certification are signaling mechanisms with which nonprofits can demonstrate their
quality. They are also a communication tool that mitigates donors’ lack of knowledge
about an NGO. In the competitive fundraising market, an unaccredited or uncertified
5
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Table 1. Transparency of Chinese NGOs (Full Marks: 100 Points).
Year
2010
2011
2012
2013
2014
2015
2016
2017
2018
2019
2020
Rater
China Philanthropic
Transparency Index
(PTI)
Grassroots NGO
Transparency Index
(GTI)
Foundation
Transparency Index
(FTI)
Average
score
Sample
size
Average
score
Sample
size
Average
score
39
33
45.1
43.11
44.1
99
1,000
500
1,000
1,000
27.23
27.87
32.44
1,000
1,300
1,738
China Charity
Information Centre
Tsinghua University
Sample
size
48.89
2,508
43.91
2,604
49.45
3,053
48.91
3,637
47.73
4,234
33.67
4,956
50.08
5,694
51.34
6,394
55.43
2,478
China Foundation
Center
Source. China Foundation Center (http://fti.foundationcenter.org.cn/PDFFile/FTI2018Conferencesy.pdf; http://fti.foundationcenter.org.cn/PDFFile/FTI2019Conference-sy.pdf; http://fti.
foundationcenter.org.cn/PDFFile/FTI2020.pdf); One Foundation (http://www.onefoundation.cn/index.
php?m=article&a=show&id=879); Peng (2014).
Note. The GTI does not include foundations. China Foundation Center rated only foundations having a
website for the year 2020. NGO = nongovernmental organization.
nonprofit that engages in best practices may not effectively distinguish itself from others that do not perform at the same standard.
Bekkers (2003) discovered that in the Netherlands, donors had higher trust in
charities and gave more money to charitable causes if they knew the CBF-Keur
accreditation system. Using a sample of 102 U.S. nonprofits, N. C. Feng et al. (2016)
found that the Standards for Excellence certification was associated with increases
in donations relative to a control group of nonprofits that did not receive the certification. Adena et al. (2019) implemented an experiment to test the impact of quality
certification on donations to charities. The result showed that participants presented
with a certified charity chose higher donations by 10% compared with the control
group that was not given such information. Considering the relatively low nonprofit
transparency in China and other authoritarian states, accreditation and certification
may offer NGOs a similar strategic advantage for fundraising. Therefore, I submit
the following hypothesis:
Hypothesis 1: Organizational legitimacy attested through nonprofit accreditation
or certification is positively related to the amount of charitable donations to NGOs.
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Nonprofit and Voluntary Sector Quarterly 00(0)
Political Connections
Under authoritarian rule where the state usually retains an important role in deciding
resource distribution for NGOs, political connections have been charged with bringing
about financial resources (e.g., Henderson, 2011; Q. Ma, 2006). Prior literature commonly studied the value of political connections for nonprofit fundraising in China within
the resource dependence framework. Cheng and Wu (2021) and Zhou and Ye (2021)
posited that political connections would enhance NGOs’ legitimacy, which in turn could
lead to more donation income. Yet scandals that occurred in politically connected NGOs
frequently made headlines. Johnson and Ni (2015) and Wei (2020) formulated political
connections as guanxi, a Chinese culture broadly defined as an informal interpersonal
relationship. However, guanxi is hidden and hard to examine (Zhou and Ye, 2021) and
does not necessarily capture the impact of formal political embeddedness (Q. Wang,
2021b). Ni and Zhan (2017) and Wei (2020) equated political connections with government control and believed such control meant greater financial opportunities for NGOs.
Their argument was theoretically grounded but unclear about how government control
can be translated into charitable donation—a source of nonprofit revenue not in the possession of the party-state.
To understand the effect of political connections on fundraising, this study adopts
an alternative approach in order to institutionally and practically examine the mechanism through which the state channels charitable donations to NGOs. Zhang et al.
(2016) observed that a large amount of corporate donations went to politically connected NGOs. They attributed this phenomenon to China’s weak market institutions.
On one hand, the Chinese government co-opts business elites by two means. First, the
state maintains control of key resources and uses them to incentivize conformity.
Second, the state seeks to incorporate business elites into the political system by
appointing them as delegates to legislative bodies. On the other hand, the state extends
its grabbing hand into the pockets of firms for charitable donations. Government officials may solicit donations through both persuasion and intimidation (L. Feng &
Zhang, 2014). The government is more likely to give preferential treatment to firms
that make such contributions than to those that do not (H. Wang & Qian, 2011).
At all administrative levels, the Chinese government frequently forces its state-salaried employees to donate to government-run charitable projects and politically connected NGOs. The donation can be a flat rate or in accordance with the employee’s
administrative rank. In 2005, many cities began launching the “donate one yuan a day”
campaign among state-salaried employees. Some local governments even deducted the
donation directly from employees’ paychecks. Those cases are prevalent rather than
sporadic (L. Feng & Zhang, 2014).3 Drawing data from the 2012 Chinese General
Social Survey, Hu and Kong (2021) found that in comparison with people working in
the private sector, employees salaried by the state and state-owned enterprises were
more likely to donate when the donation was either suggested or coerced by government and less likely to donate when the donation was voluntary.
In her analysis of government-NGO relations, Xu (2008) identified three ways in
which the government helped the government-organized China Population Welfare
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7
Foundation (CPWF) fundraise. First, government officials sometimes personally
availed themselves of fundraising activities. Second, the CPWF and its supervisory
agency—the State Population Office—mobilized government and public service unit
(shiye danwei) employees to donate. Third, the CPWF activated the State Population
Office’s more than one million branches and 80 million individual and organizational
members across the country to fundraise.
Similarly, three fourths of the surveyed Russian philanthropists reported experiencing pressure from local authorities to donate to designated recipients (Livshin & Weitz,
2006). In Vietnam, compulsory giving includes (1) government employees are required
to contribute to government-affiliated charities, (2) households and private businesses
are visited by local officials and mass organizations for charitable contributions, and (3)
community members are asked to support local charities on an annual or biannual basis
(Nguyen & Doan, 2015). In these cases, political connections grant NGOs the privilege
of raising donations that they otherwise would not have raised. Therefore, I submit the
following hypothesis:
Hypothesis 2: Political connections are positively related to the amount of charitable donations to NGOs.
Moderating Effect of Organizational Legitimacy
Against the backdrop of interrupted associational life and a stagnant economy, in the
late 1970s, Chinese NGOs emerged as the state’s policy coordination intermediaries
and fundraising arms in a top-down manner. Three factors rendered competition for
nonprofit resources almost irrelevant: the small number of NGOs, the large employment in public organizations and state-owned enterprises, and prevention of a second
NGO working on similar issues from registering in each administrative jurisdiction.
Organizational legitimacy, if any, would be the leadership of “old revolutionaries” and
their spouses or children who enjoyed the admiration of the people who retained a
fresh memory of the Anti-Japanese War (Q. Wang, 2021a). Such leadership, however,
did not equate conformity, competence, or accountability.
With the introduction of the concept of “NGO” to the Chinese society in the late 1990s,
more and more people and groups began seeking NGO registration. Among the founders,
some had been government officials who used their institutional experience to build partnerships with the state (Hsu & Jiang, 2015). Other founders, especially those without such
experience, often pursued political embeddedness by instituting themselves in a stateendorsed organization or by inviting government officials to their boards (Ho, 2007).
These political connections were believed to place NGOs in an advantageous position in
various ways.
Chinese NGOs grew rapidly in the 2000s. Concurrently, the burgeoning private
economy relaxed public sector employment and people’s dependence on the state.
Political leadership in the nonprofit sector no longer enjoyed the legitimacy derived
from the war times. As nonprofit sector scandals made headlines, China began enacting regulations to standardize the nonprofit sector like other authoritarian states
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(Henderson, 2011; Richter & Hatch, 2013). NGOs needed to adapt to the new environment in which they competed for limited nonprofit resources by, for example, strengthening legitimacy other than, if not on top of, political connections.4 Newly emerged
accreditation and certification programs that signal legitimacy can potentially moderate the effects of political connections.
While all NGOs can voluntarily pursue accreditation and certification, which in turn
increases their competitiveness in fundraising, the effect could be stronger for NGOs that
have no or weak political connections. That is, being accredited or certified would reduce
the gap between the amounts of charitable donations attributable to political connections.
First, politically connected NGOs are more likely to mimic governmental structure and
operate in a centralized, bureaucratic manner (Toepler & Fröhlich, 2020) that alienates
potential donors. For example, Nubo Huang, a Chinese entrepreneur said he did not want
to donate to government-organized NGOs for the above reasons.5 Moreover, in the digital
age, the internet sometimes fosters an anti-authority culture. NGOs showing off their
political connections “may be inviting more enemies than donors” (Zhou & Ye, 2021, p.
501). Second, when having no or weak political connections, NGOs could operate free
from direct government control and have more autonomy in planning their boards, programs, and fundraising. They are more likely to network with other organizations to gain
information and broker resources (Li et al., 2018). Without a commandable donor base,
they have no option but to maximize the value of accreditation or certification to motivate
potential donors, especially small donors who have become increasingly important and
who pay attention to organizational legitimacy (Zhou & Ye, 2021).
As a result, although accreditation and certification enhance NGOs’ legitimacy sectorwise, they benefit NGOs differently. Put another way, organizational legitimacy attested
through accreditation and certification may discount the value of political connections in
nonprofit resource acquisition, offering NGOs with no or weak political connections an
alternative funding opportunity. Therefore, I submit the following hypothesis:
Hypothesis 3: Organizational legitimacy attested through nonprofit accreditation
or certification negatively moderates the relationship between political connections
and the amount of charitable donations to NGOs.
Method
Research Context
Chinese foundations are the subjects under study. By the end of 2019, 15 years after
the promulgation of the 2004 Regulations for the Management of Foundations, the
number of foundations had reached 7,585 (see Table 2). Charitable donations to
Chinese foundations increased from 34.05 billion yuan to 67.71 billion yuan from
2010 to 2019. They surpassed the China Charity Federation system to receive the
most charitable donations from no later than 2010. During 2008–2013, donations
accounted for approximately 84% of their total annual revenue (Q. Wang & He,
2018). Albeit only one segment of China’s nonprofit sector, foundations’ similarities
with other forms of NGOs are more salient than their differences.
9
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Table 2. Charitable Donations Received by Chinese Foundations.
Year
Number of
foundations
Donation to foundations
(in billion yuan)
Donation to foundations /
National total
2004
2005
2006
2007
2008
2009
2010
2011
2012
2013
2014
2015
2016
2017
2018
2019
892
975
1,144
1,340
1,597
1,843
2,202
2,614
3,029
3,549
4,117
4,784
5,559
6,307
7,034
7,585
34.05
33.70
30.57
37.35
38.32
44.56
62.55
65.80
64.59
67.71
33.00%
39.88%
37.42%
37.74%
36.76%
40.19%
44.91%
43.87%
44.88%
44.86%
Source. China Charity Federation (http://www.cncf.org.cn/storage/ueditor/file/2020/09/19/39c9155e41612
e431eb076253d1777ec.pdf); China Statistical Yearbooks; Q. Wang (2020).
Note. The exchange rate between U.S. dollars and Chinese yuan during this period was roughly 1:6.5.
Data and Sample
The study used data from three data sources, resulting in a sample of 2,021 foundations or 66.72% of the foundations established before 2013.6 The first source
was the Research Infrastructure of Chinese Foundations (RICF), which holds
records of 3,342 foundations’ organizational, personnel, financial, and program
information for the year 2013 (see the data descriptor by J. Ma et al., 2017). The
other two sources were Q. Wang’s (2018a) data for 4,229 foundations’ link with
the state and Q. Wang’s (2018b) typological study of 3,342 foundations, in which
the foundations were divided into government-created and other groups.
Foundations registered in 2013 were removed from the sample because some
foundations registered that year reported donation income for the purpose of registration. These numbers did not reflect a foundation’s fundraising ability under
normal operation.
Dependent Variable
The dependent variable was the amount of charitable donations a foundation received
in 2013. Because the distribution of charitable donations was skewed, I took the natural logarithm of this variable (see the histogram in the Supplemental Online Material).
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Independent Variables
Organizational legitimacy. The Chinese government administratively established
three voluntary certification programs for NGO legitimacy in the 2000s. The first
was the nonprofit evaluation (shehui zuzhi pinggu). It is a comprehensive assessment of social organizations’ (what NGOs are called in China) basic organizational
condition (jichu tiaojian), governance (neibu zhili), effectiveness (gongzuo jixiao),
and societal recognition (shehui pingjia) measured by comments from internal and
external stakeholders. Each administrative jurisdiction sets up an expert committee
comprising government officials, researchers, lawyers, accountants, and practitioners to conduct on-site evaluation. Then a review committee further examines the
evaluation result.
The nonprofit evaluation rates NGOs from 1A to 5A. A higher score means better
performance; 3A and above indicate the government’s recognition of an NGO’s performance. According to the RICF, by 2013 roughly 20% (646 out of 3,342) of the
foundations had self-selected to participate in this evaluation, and about 17.5% (or
586) were awarded 3A or above. Although the participation rate was relatively low in
2013, a good evaluation score could still provide positive signals to potential donors.
The results remain effective for 5 years.
The other two certification programs concern nonprofit tax qualification. In China,
NGOs do not automatically obtain nonprofit tax qualifications upon registration; they
must apply. In the 2000s, the Chinese government began to regulate nonprofit tax
exemption (charitable donations being nontaxable) and pretax deduction (deduction of
donation from donors’ income before tax). Before applying for the tax exemption
qualification, NGOs must have demonstrated conformity to financial requirements,
such as proper use of funds and reasonable salary and benefits. The pretax deduction
qualification highlights operational conformity. For example, an administrative penalty disqualifies an NGO for this qualification for 3 years.
The two tax qualifications offer incentives to donors. The nonprofit tax exemption
qualification indicates a possible higher proportion of donations for program implementation. The RICF reports that in 2013 about 56% (or 1,886) of the foundations had
obtained this qualification. It also reports that in the same year about 21% (or 717) of
foundations had obtained the nonprofit pretax deduction qualification. At that time,
the Enterprise Income Tax Law permitted donations of up to 3% of firms’ profits to be
deductible in the calculation of their taxable income. The two tax qualifications are
effective for 5 years and 3 years, respectively.
The certifying agencies must publicize nonprofit evaluation scores and tax qualifications on official websites. The three certification programs are visible proxy for
organizational legitimacy in China’s nonprofit sector. Nonprofit evaluation score was
coded as an interval variable ranging from 0 to 5, where 0 meant a foundation had not
been rated yet and 1–5 corresponded to 1A–5A. This variable denotes the extent to
which an NGO has proved its legitimacy via certification. The two tax qualifications
each were coded as a dummy variable, where 1 meant a foundation had obtained the
qualification and 0 if not.
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11
Political connections. Prior literature usually operationalizes political connections in
two ways. First is the number or presence of government officials on an NGO’s
board of directors (e.g., Cheng & Wu, 2021; Johnson & Ni, 2015). This study
adopted the number of government officials (see a discussion on the presence of
government officials in the Supplemental Online Material). Second is to code
NGOs’ political connections as their formal affiliation with the state—either existent or nonexistent. Such operationalization does not fully address the fact that the
nature, formation, and degree of political affiliation may result in different dynamics between the state and NGOs.
Presently in China, both government agencies and public service units (PSUs) are
frequent founders of NGOs. The term government agencies refers to administrative
agencies, legislatures, law enforcement agencies, mass organizations, and democratic
parties submitting to the leadership of the Chinese Communist Party (CCP) (Ni &
Zhan, 2017; Q. Wang, 2018a). PSUs are quasi-government agencies under the purview of the state (Pearson, 2007). Typical PSUs include universities, hospitals, parks,
and museums. They provide services in education, science and technology, culture,
and sanitation using state-owned assets.
The state controls PSUs in several ways. First, the state is the de facto sole creator
of PSUs. The Interim Regulation on the Registration of Public Service Units (2004)
allows “other organizations” to establish PSUs with state-owned assets, but it is practically impossible to find PSUs established by other organizations. Second, executives
of these agencies are usually appointed by a corresponding CCP organization department. They bear comparable administrative ranks to their peers in government agencies and are transferable from and to governmental positions. Third, PSU employees
are often salaried by the state and depend on the state for inexpensive housing, health
care, and pensions. PSUs are part of the state and complement the government’s work.
Kang (2018) made it explicit that political connections are related to the government’s treatment of NGOs, including resources, trust, and duties. He noted that the
new blueprint for the intended relations between the party-state and businesses, nonprofits, and individuals is that the party-state is in the center and the rest are “ranked
in order as a series of concentric rings. . . . [T]his hierarchical civil administration
system was under the charge of the ruling party and was operated by the government”
(p. 4). Figure 1 graphically illustrates such relations.
Quasi-government agencies are common in many countries. For example, the Russian
government has decentralized tasks to quasi-government agencies like those in China in
that those agencies are under the auspices of the state and complement the government’s
work (Peregudov & Semenenko, 1996). Since quasi-government and government agencies bear different functions and closeness to the state, distinguishing between NGOs’
affiliation with the state is more revealing than regarding them as homogeneous government-organized NGOs. Political affiliation was therefore coded into a categorical variable that took the value of 1 for foundations being civic, meaning the absence of formal
affiliation with the state; 2 for quasi-governmental affiliation; and 3 for governmental
affiliation. Civic foundations were treated as the reference category.
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Figure 1. Political connections and the distribution of resources, trust, and duties.
Note. Grassroots NGOs in this figure refers to unregistered NGOs.
Control Variables
Organizational variables. Age represents the years a foundation has existed. Previous
research shows that age could be positively tied to the amount of charitable donations
a nonprofit received (Fischer et al., 2011). A larger board size may increase the board’s
access to external resources (Guo, 2007). Professionalization is important for fundraising (Hwang & Powell, 2009) and is measured by the number of full-time employees. I took the natural logarithm of full-time employees to reduce skewness.
The Regulations for the Management of Foundations classified foundations as public
or nonpublic upon registration. Only the former, given their public fundraising qualification, can fundraise from the public. The attainment of this qualification was coded as 1;
otherwise 0.7 The Regulations also stipulated a registration system that defines foundations’ scope of operation as either national (coded as 1) or subnational (coded as 0). If a
foundation works on issue areas enumerated in the Charity Law such as poverty alleviation, education, health, and so on, it was coded as 1; otherwise 0. Finally, university
foundations developed rapidly and attracted large amounts of donations from alumni and
entrepreneurs. To account for their special status in the nonprofit resource market, university foundations entered the regression in the value of 1; otherwise 0.8
Financial variables. Saxton and Wang (2014) found that fundraising expenditure is positively related to nonprofits’ donation income. Total assets 2012 measured organizational
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13
size. Fischer et al. (2011) found a negative relationship between nonprofits’ total assets
of the preceding fiscal year and charitable donations. The two financial variables were
logged due to high skewness.
Contextual variables. The first was the 2013 nonprofit policy environment index developed by the China Philanthropy Research Institute (Z. Wang et al., 2016), which rates the
supportiveness of nonprofit policy in each province. Economic development may affect
resource availability. The 2013 provincial GDP per capita captured regional economy.
Analytical Strategy
This study adopted the ordinary least squares (OLS) regression as Johnson and Ni
(2015) and Ni and Zhan (2017) did to log-transformed charitable donations that
Chinese foundations received. In addition, the double-hurdle model, among two other
alternatives, was implemented to account for the fact that a nontrivial portion of the
sampled foundations—20.3% or 410 in number—reported a zero amount of donation
income. The Tobit model assumes that zero observations are standard corner solutions,
requiring that the receipt and amount of charitable donations be determined by the
same process. The Heckman model assumes foundations that were selected to be
recipients would receive a nonzero amount.
The double-hurdle model nests the above two censoring mechanisms together (Li
et al., 2020) and relaxes their assumptions (Forbes & Zampelli, 2011). Its specification
undertakes a two-step estimation procedure: probit regression in the first step and
linear regression in the second step. It requires two hurdles be overcome to observe
positive values. Stated in terms of fundraising, a foundation must cross the first hurdle
(1H) to be identified as a potential recipient and then the second hurdle (2H) to receive
nonzero. The model allows the same factor to affect the receipt and amount of charitable donations in different ways. This flexibility accords with the reality that a potential recipient identified in the first step may receive a zero donation in the second step.
In the following analysis, both OLS and double-hurdle models used robust standard
errors to correct for heteroscedasticity.
Results
Table 3 provides the descriptive statistics. Table 4 presents the regression results.
The OLS model (Model 1) showed that the three organizational legitimacy variables were positively related to charitable donations at p < .05 or lower. In the doublehurdle model (Models 2–3), nonprofit evaluation score was not tied to the probability
of receiving charitable donations but was positively tied to the amount that donationreceiving foundations received at p < .05. Nonprofit tax exemption qualification and
pretax deduction qualification predicted greater probability and amount of charitable
donations at p < .05 or lower. Political connections, namely the number of government officials and quasi-governmental and governmental affiliations, were insignificant in both models. To assess the regressors in the double-hurdle model, it is helpful
14
Nonprofit and Voluntary Sector Quarterly 00(0)
Table 3. Descriptive Statistics.
Variable
Charitable donations
Charitable donations (logged)
(H1) Nonprofit evaluation score
(H1) Nonprofit tax exemption
(H1) Nonprofit pretax deduction
(H2) Number of government
officials
(H2) Political affiliation
1-Civic
2-Quasi-governmental
3-Governmental
Age
Board size
Full-time employees
Full-time employees (logged)
Public fundraising qualification
Scope of operation
Issue area
University foundation
Fundraising expenditure
Fundraising expenditure (logged)
Total assets 2012
Total assets 2012 (logged)
Nonprofit policy environment
GDP per capita
Observation
Mean
2,021
2,021
2,021
2,021
2,021
1,928
12,491
6.094
0.979
0.271
0.701
0.573
2,021
599
408
1,014
2,021
1,911
2,019
2,019
2,021
2,021
2,021
2,021
2,021
2,021
2,021
2,021
2,021
2,021
2.205
7.808
13.114
3.714
1.144
0.454
0.080
0.880
0.117
42.28
0.650
37,876
9.208
0.486
61.923
Standard
deviation
70,203
3.590
1.654
1.473
Minimum Maximum
0
0
0
0
0
0
1
7.458
6.480
6.205
0.863
578.44
1.531
150,599
1.423
0.164
21.395
1
5
0
0
0
0
0
0
0
0
3.69
1.545
0.110
22.921
1,608,360
14.291
5
1
1
16
3
32
25
111
4.718
1
1
1
1
18,962
9.850
2,871,878
14.87
0.803
99.607
Note. All monetary values are in 1,000 Chinese yuan.
to analyze their marginal effects (see the last column in Table 4), which can be compared with OLS coefficients that are directly interpreted as marginal effects (Newman
et al., 2003). In terms of the impact on the dependent variable, the organizational
legitimacy and political connections variables exhibited similar significance and
weight between the two regression methods. Therefore, Hypothesis 1 was supported;
Hypothesis 2 was not.
Tables 5–7 present the interaction effects between organizational legitimacy and
political affiliation. All three OLS models (Models 4, 7, and 10) showed negative, significant interaction terms between each organizational legitimacy variable and the two
forms of political affiliation at p < .1 or lower. According to Models 5 and 6, the interaction between nonprofit evaluation score and quasi-governmental affiliation reported a
negative effect only on the probability of receiving charitable donations at p < .1. The
interaction between nonprofit evaluation score and governmental affiliation reduced the
15
Wang
Table 4. OLS and Double-Hurdle Models for Charitable Donations (Logged).
Double-hurdle
Organizational legitimacy
(H1) Nonprofit evaluation score
(H1) Nonprofit tax exemption
(H1) Nonprofit pretax deduction
Political connections
(H2) Government officials
(H2) Quasi-governmental
affiliation (QA)
(H2) Governmental affiliation
(GA)
Age
Board size
Full-time employees (logged)
Public fundraising qualification
Scope of operation
Issue area
University foundation
Fundraising expenditure (logged)
Total assets 2012 (logged)
Nonprofit policy environment
GDP per capita
Constant
R2
F
Pseudo R2
Chi2
OLS
1H: Receipt
2H: Amount
Marginal effects
Model 1
Model 2
Model 3
dy/dx
0.103*
(0.052)
0.582***
(0.180)
1.052***
(0.178)
0.027
(0.026)
0.211*
(0.099)
0.272***
(0.079)
0.060*
(0.029)
0.293**
(0.103)
0.636***
(0.106)
0.096†
(0.051)
0.603***
(0.184)
1.007***
(0.169)
−0.072
(0.051)
0.095
(0.263)
−0.126
(0.291)
−0.060***
(0.012)
0.031*
(0.013)
0.330**
(0.108)
0.474†
(0.282)
1.239***
(0.311)
1.183***
(0.275)
1.577***
(0.280)
0.293***
(0.047)
0.279***
(0.079)
0.459
(0.494)
0.009*
(0.004)
−0.080
(0.725)
0.226
40.310***
−0.022
(0.024)
0.178
(0.142)
−0.097
(0.132)
−0.017**
(0.005)
0.014*
(0.006)
0.086†
(0.051)
0.099
(0.126)
0.297†
(0.176)
0.223*
(0.113)
0.763***
(0.208)
0.133***
(0.034)
−0.058†
(0.033)
−0.017
(0.254)
0.004*
(0.002)
0.435
(0.321)
−0.032
(0.028)
−0.230
(0.165)
0.063
(0.175)
−0.033***
(0.007)
0.006
(0.007)
0.264***
(0.059)
0.307†
(0.172)
0.691***
(0.178)
0.933***
(0.172)
0.763***
(0.178)
0.120***
(0.027)
0.492***
(0.053)
0.355
(0.303)
0.002
(0.002)
0.858†
(0.486)
−0.065
(0.048)
0.087
(0.256)
−0.124
(0.283)
−0.057***
(0.011)
0.029*
(0.012)
0.367***
0.103
0.432
(0.265)
1.071***
(0.309)
1.140***
(0.248)
1.714***
(0.260)
0.332***
(0.062)
0.299***
(0.077)
0.259
(0.511)
0.010*
(0.004)
0.106
907.280***
Note. Observation: 1,824. dy/dx for factor levels is the discrete change from the base level. OLS = ordinary least
squares; QA = quasi-governmental affiliation; GA = governmental affiliation; GDP = gross domain product.
†
p < .1. * p < .05. ** p < .01. *** p < .001.
16
Nonprofit and Voluntary Sector Quarterly 00(0)
probability at p < .01 but increased the amount to donation-receiving foundations at p <
.05. In Models 8 and 9, the significant interaction term that led to lower probability of
receiving charitable donations could be found only between nonprofit tax exemption
qualification and governmental affiliation at p < .05. Models 11 and 12 reported two
negative, significant interaction terms for the receipt of charitable donations between
nonprofit tax deduction qualification and quasi-governmental and governmental affiliation at p < .01 or lower, respectively. In Models 10 and 11, the coefficients for quasigovernmental affiliation were positive, significant at p < .001. Interaction terms in these
two models might indicate pretax deduction qualification’s offsetting effect on such
affiliation. None of the interaction terms between the number of government officials
and the three organizational legitimacy variables was reliably significant at p < .1 (see
the Supplemental Online Material). Thus, Hypothesis 3 received limited support.
Yet it is difficult to understand the interaction effects based on the coefficients alone
since the interaction analysis involved multiple regression methods and both the probability and size of charitable donations. Therefore, it is beneficial to visualize these
interaction terms (see Figures 2 to 4; also see predictive margins of political affiliation
in the Supplemental Online Material) and interpret the marginal effects of political
affiliation conditional on organizational legitimacy (see Table 8).
As shown by the OLS and double-hurdle models in Figure 2, political affiliation
tended to make a negative difference when nonprofit evaluation score was relatively
high. The evidence is strong for the comparison between governmental and civic foundations that were awarded 4A or 5A status. Figure 3 shows that governmental foundations who had obtained the nonprofit tax exemption qualification received a
significantly lower amount of charitable donations than civic foundations. Figure 4
reveals that without the nonprofit pretax deduction qualification, quasi-governmental
foundations would receive more charitable donations than civic foundations. However,
after these two types of foundations obtained this qualification, the gap became insignificant. In sum, nonprofit certification programs can lift the amount of charitable
donations to civic foundations more than to politically affiliated foundations to the
extent that (1) civic foundations would receive more charitable donations than governmental foundations or (2) the gap between civic and quasi-governmental foundations
was greatly reduced. This pattern, however, did not reliably exist for the number of
government officials (see marginal effects of the number of government officials in
the Supplemental Online Material).
The results for control variables were relatively reliable across all models. Full-time
employees (logged), public fundraising qualification, scope of operation, issue area, university foundation, and fundraising expenditure (logged) all predicted more charitable
donations at p < .1 or lower, consistent with the expectation in the OLS and doublehurdle models. Age was negatively tied to charitable donations. Future research can help
determine whether younger foundations have implemented more innovative fundraising
strategies. Total assets 2012 (logged) were positively related to the amount of charitable
donations. Probably instead of penalizing those that had been accumulating wealth,
Chinese donors believed larger foundations were more credible. However, this variable
17
Wang
Table 5. Interactions Between Nonprofit Evaluation Score and Political Affiliation.
Double-hurdle
Organizational legitimacy
(H1) Nonprofit evaluation score
(H1) Nonprofit tax exemption
(H1) Nonprofit pretax deduction
Political connections
(H2) Government officials
(H2) Quasi-governmental affiliation (QA)
(H2) Governmental affiliation (GA)
Interactions
(H3) Political Affiliation × Evaluation
QA × Nonprofit Evaluation Score
GA × Nonprofit Evaluation Score
Age
Board size
Full-time employees (logged)
Public fundraising qualification
Scope of operation
Issue area
University foundation
Fundraising expenditure (logged)
Total assets 2012 (logged)
Nonprofit policy environment
GDP per capita
Constant
R2
F
Pseudo R2
Chi2
OLS
1H: Receipt
2H: Amount
Model 4
Model 5
Model 6
0.240***
(0.072)
0.580***
(0.180)
1.048***
(0.179)
0.16***
(0.050)
0.209*
(0.100)
0.273***
(0.079)
0.002
(0.046)
0.286**
(0.103)
0.626***
(0.106)
−0.073
(0.051)
0.276
(0.280)
0.035
(0.311)
−0.023
(0.024)
0.264†
(0.149)
0.019
(0.137)
−0.032
(0.028)
−0.248
(0.172)
−0.042
(0.185)
−0.216*
(0.099)
−0.180†
(0.098)
−0.059***
(0.013)
0.031*
(0.013)
0.333**
(0.107)
0.480†
(0.282)
1.252***
(0.312)
1.193***
(0.277)
1.600***
(0.281)
0.297***
(0.047)
0.278***
(0.079)
0.434
(0.493)
0.009*
(0.004)
−0.184
(0.728)
0.227
37.490***
−0.139†
(0.084)
−0.179**
(0.057)
−0.016**
(0.005)
0.014*
(0.006)
0.096†
(0.051)
0.111
(0.127)
0.305†
(0.179)
0.237*
(0.113)
0.776***
(0.206)
0.139***
(0.034)
−0.058†
(0.033)
−0.014
(0.255)
0.004†
(0.002)
0.348
(0.320)
0.012
(0.065)
0.111*
(0.056)
−0.035***
(0.008)
0.006
(0.007)
0.262***
(0.059)
0.293†
(0.172)
0.660***
(0.179)
0.922***
(0.171)
0.758***
(0.177)
0.119***
(0.026)
0.498***
(0.053)
0.342
(0.303)
0.003
(0.002)
0.871†
(0.489)
0.107
921.860***
Note. Observation: 1,824. OLS = ordinary least squares; QA = quasi-governmental affiliation; GA = governmental
affiliation; GDP = gross domain product.
p < .1. * p < .05. ** p < .01. *** p < .001.
†
18
Nonprofit and Voluntary Sector Quarterly 00(0)
Table 6. Interactions Between Nonprofit Tax Exemption Qualification and Political Affiliation.
Double-hurdle
Organizational legitimacy
(H1) Nonprofit evaluation score
(H1) Nonprofit tax exemption
(H1) Nonprofit pretax deduction
Political connections
(H2) Government officials
(H2) Quasi-governmental affiliation (QA)
(H2) Governmental affiliation (GA)
Interactions
(H3) Political Connections × Exemption
QA × Nonprofit Tax Exemption
GA × Nonprofit Tax Exemption
Age
Board size
Full-time employees (logged)
Public fundraising qualification
Scope of operation
Issue area
University foundation
Fundraising expenditure (logged)
Total assets 2012 (logged)
Nonprofit policy environment
GDP per capita
Constant
R2
F
Pseudo R2
Chi2
OLS
1H: Receipt
2H: Amount
Model 7
Model 8
Model 9
0.102*
(0.052)
1.044***
(0.27)
1.051***
(0.178)
0.027
(0.026)
0.466**
(0.160)
0.271***
(0.079)
0.060*
(0.029)
0.411*
(0.161)
0.637***
(0.105)
−0.075
(0.051)
0.291
(0.299)
0.076
(0.316)
−0.025
(0.024)
0.241
(0.158)
−0.014
(0.138)
−0.032
(0.028)
−0.170
(0.179)
0.121
(0.188)
−0.614†
(0.371)
−0.774*
(0.389)
−0.058***
(0.013)
0.032*
(0.013)
0.338**
(0.108)
0.481†
(0.284)
1.261***
(0.315)
1.217***
(0.276)
1.579***
(0.281)
0.289***
(0.047)
0.279***
(0.079)
0.471
(0.499)
0.009*
(0.004)
−0.284
(0.737)
0.227
36.620***
−0.248
(0.298)
−0.443*
(0.205)
−0.016**
(0.005)
0.014*
(0.006)
0.091†
(0.051)
0.105
(0.126)
0.313†
(0.179)
0.238*
(0.113)
0.759***
(0.209)
0.133***
(0.034)
−0.057†
(0.033)
0.002
(0.259)
0.004*
(0.002)
0.349
(0.324)
−0.171
(0.241)
−0.193
(0.219)
−0.033***
(0.007)
0.007
(0.007)
0.267***
(0.060)
0.308†
(0.172)
0.693***
(0.181)
0.943***
(0.172)
0.763***
(0.178)
0.119***
(0.027)
0.492***
(0.053)
0.353
(0.306)
0.002
(0.002)
0.800
(0.498)
0.106
908.800***
Note. Observation: 1,824. OLS = ordinary least squares; QA = quasi-governmental affiliation; GA = governmental
affiliation; GDP = gross domain product.
†
p < .1. * p < .05. ** p < .01. *** p < .001.
19
Wang
Table 7. Interactions Between Nonprofit Pretax Deduction Qualification and Political Affiliation.
Double-hurdle
Organizational legitimacy
(H1) Nonprofit evaluation score
(H1) Nonprofit tax exemption
(H1) Nonprofit pretax deduction
Political connections
(H2) Government officials
(H2) Quasi-governmental affiliation (QA)
(H2) Governmental affiliation (GA)
Interactions
(H3) Political Connections × Deduction
QA × Nonprofit Pretax Deduction
GA × Nonprofit Pretax Deduction
Age
Board size
Full-time employees (logged)
Public fundraising qualification
Scope of operation
Issue area
University foundation
Fundraising expenditure (logged)
Total assets 2012 (logged)
Nonprofit policy environment
GDP per capita
Constant
R2
F
Pseudo R2
Chi2
OLS
1H: Receipt
2H: Amount
Model 10
Model 11
Model 12
0.096†
(0.052)
0.562**
(0.179)
1.851***
(0.327)
0.027
(0.026)
0.199*
(0.099)
0.658***
(0.142)
0.058*
(0.029)
0.292**
(0.103)
0.650***
(0.188)
−0.071
(0.051)
1.272***
(0.388)
0.487
(0.412)
−0.022
(0.024)
0.770***
(0.219)
0.181
(0.167)
−0.032
(0.028)
−0.116
(0.242)
0.032
(0.243)
−1.704***
(0.417)
−0.891*
(0.397)
−0.058***
(0.012)
0.032*
(0.013)
0.328**
(0.107)
0.469†
(0.283)
1.239***
(0.308)
1.181***
(0.276)
1.680***
(0.280)
0.295***
(0.046)
0.290***
(0.079)
0.487
(0.492)
0.009*
(0.004)
−0.745
(0.762)
0.231
36.670***
−0.933***
(0.261)
−0.470**
(0.170)
−0.016**
(0.005)
0.015*
(0.006)
0.086†
(0.051)
0.102
(0.126)
0.293†
(0.176)
0.221*
(0.113)
0.832***
(0.214)
0.136***
(0.033)
−0.054
(0.034)
−0.004
(0.255)
0.004*
(0.002)
0.156
(0.331)
−0.169
(0.258)
0.047
(0.239)
−0.033***
(0.007)
0.006
(0.007)
0.264***
(0.059)
0.303†
(0.172)
0.689***
(0.178)
0.93***
(0.172)
0.785***
(0.177)
0.121***
(0.027)
0.493***
(0.053)
0.351
(0.304)
0.002
(0.002)
0.841
(0.514)
0.108
906.110***
Note. Observation: 1,824. OLS = ordinary least squares; QA = quasi-governmental affiliation; GA = governmental
affiliation; GDP = gross domain product.
†
p < .1. * p < .05. ** p<.01. *** p<.001.
20
Nonprofit and Voluntary Sector Quarterly 00(0)
Figure 2. Interaction effects between nonprofit evaluation score and political affiliation with
95% confidence intervals.
Note. The horizontal line represents civic foundations, the reference category.
slightly reduced the probability of receiving charitable donations (see Models 2, 5, and
8). In double-hurdle models, board size and GDP per capita predicted whether a foundation would receive charitable donations but not the size of the donations. However, the
two variables had similar marginal effects as in the OLS model (see Table 1). Nonprofit
policy environment remained insignificant throughout the analysis.
Discussion
The sample of Chinese foundations and the research presented in this study indicate
the extent to which organizational legitimacy attested through voluntary certification,
Wang
21
Figure 3. Interaction effects between nonprofit tax exemption qualification and political
affiliation with 95% confidence intervals.
Note. The horizontal line represents civic foundations, the reference category.
political connections, and their interactions are related to nonprofit fundraising under
authoritarianism. The evidence shows that all the three certification programs, namely
nonprofit evaluation, tax exemption qualification, and pretax deduction qualification
can help foundations attract more charitable donations. This study distinguishes
between individual and organizational political connections. Individual political connections or the number of government officials serving as managerial board members
did not predict more charitable donations. There are two plausible reasons. First, while
on the board, government officials had not developed a strong sense of identity and
consequentially did not fulfill their expected function (Guo & Lai, 2019). Second,
government officials were no longer as active in fundraising as before because the
22
Nonprofit and Voluntary Sector Quarterly 00(0)
Figure 4. Interaction effects between nonprofit pretax deduction qualification and political
affiliation with 95% confidence intervals.
Note. The horizontal line represents civic foundations, the reference category.
party-state had increasingly discouraged them from joining NGOs. Therefore, what
(Xu, 2008) documented in her case study might have reduced in scale.
Organizational political connections or affiliation was operationalized as a categorical variable. The separation of the two levels of political affiliation—quasi-governmental and governmental—offered nuances for their influence on fundraising.
Although neither form of affiliation led to more charitable donations than civic foundations, they interacted with organizational legitimacy differently. In addition, if university foundation were removed from the regression, quasi-governmental foundations
would have received more charitable donations than civic foundations. This is because
most Chinese universities are PSUs in nature. They have a large physical presence
23
Wang
Table 8. Average Marginal Effects of Political Affiliation on Charitable Donations (logged).
Quasi-governmental = 2
Model variance covariance
matrix of the estimators
(VCE): Robust
Civic foundations = 1
Nonprofit evaluation score
0
1
2
3
4
5
Nonprofit tax exemption
0
1
Nonprofit pretax deduction
0
1
Governmental = 3
OLS
Double-hurdle
OLS
Double-hurdle
dy/dx
dy/dx
dy/dx
dy/dx
(base
outcome)
(base
outcome)
(base
outcome)
(base outcome)
0.276
(0.280)
0.060
(0.263)
−0.155
(0.282)
−0.371
(0.330)
−0.587
(0.398)
−0.803†
(0.477)
0.233
(0.277)
−0.009
(2.257)
−0.213
(0.301)
−0.379
(0.376)
−0.510
(0.460)
−0.609
(0.547)
0.035
(0.311)
−0.145
(0.290)
−0.326
(0.302)
−0.506
(0.341)
−0.686†
(0.402)
−0.866†
(0.475)
−0.001
(0.304)
−0.228
(0.283)
−0.421
(0.298)
−0.577†
(0.335)
−0.698†
(0.384)
−0.789†
(0.443)
0.291
(0.299)
−0.323
(0.345)
0.263
(0.293)
−0.314
(0.389)
0.076
(0.316)
−0.697†
(0.400)
0.069
(0.307)
−0.791*
(0.392)
1.272***
(0.388)
−0.432
(0.291)
1.188**
(0.388)
−0.493
(0.301)
0.487
(0.412)
−0.404
(0.309)
0.402
(0.403)
−0.411
(0.293)
Note. Observation: 1,824. dy/dx for factor levels is the discrete change from the base level. VCE =
variance covariance matrix of the estimators; OLS = ordinary least squares.
†
p < .1. * p < .05. ** p < .01. *** p < .001.
visible to the public and through foundations promote their function as higher education providers over their political identity as PSUs. In this sense, quasi-governmental
affiliation plays a subtle role.
The above findings have wide implications for the authoritarian world. The first
implication is about the nature of donations. States do not directly control charitable
contributions. To help an NGO, governments need to utilize their authority to mobilize
donations. Although states may privilege politically connected NGOs with fundraising
advantage, they have been more successful in pressing certain individuals and organizations to donate than engaging a wide donor base. It is also possible that these NGOs
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Nonprofit and Voluntary Sector Quarterly 00(0)
have developed alternative sources of revenue, such as government subsidies and market returns (Ni & Zhan, 2017).
The second implication relates to donors and incentives. Despite low transparency in many authoritarian states’ nonprofit sectors, donors may have become
increasingly capable of perceiving NGO legitimacy. They do not necessarily
embrace state-centered charity enthusiastically (Li et al., 2020) or assign legitimacy to NGOs’ political connections. Indeed, major scandals usually occurred in
politically connected NGOs rather than in civic NGOs in regions such as Eastern
Europe, Central Asia, Russia, and China (Smith et al., 2018). Furthermore, different from voluntary accreditation and certification programs administered by thirdparty watchdogs, governments can embed incentives in government-led programs
through legislative and administrative requirements. This is especially true for the
nonprofit pretax deduction qualification whose large coefficients might be a combined effect of perceived legitimacy and built-in incentives that cannot be disentangled with the current data. We may anticipate growing importance of this
qualification because in 2018 the revised Enterprise Income Tax Law allowed corporate donations to be deductible up to 12% of firms’ profits and the excess to be
carried forward to the same extent over the next 3 years.
The interaction analysis provided evidence that under certain circumstances organizational legitimacy could negatively moderate the relationship between political
affiliation and the amount of charitable donations. The three certification programs
helped civic foundations raise more charitable donations than governmental and quasigovernmental foundations to varying degrees. Specifically, among foundations that
were awarded an evaluation score of 1A or above or obtained either of the two tax
qualifications, all the marginal effects except one in the OLS model were negative (see
Table 8), and several were significant. The findings suggest the emergence of multiple,
interactive patterns of fundraising that highlight the importance of organizational
legitimacy and resource opportunities for civic foundations. The significant direct and
indirect effect of organizational legitimacy led to the agreement with Cheng and Wu
(2021, p. 56) that foundations were “able to survive and attract resources regardless of
the status of their political connections.”
However, in light of recent global experiences, we may be wise not to rush in
assuming the dominance of organizational legitimacy in fundraising. Although the
literature depicts a trend of closing civil society under authoritarianism (Heiss, 2019),
more recent literature argues that the space for civil society may be changing or shifting rather than closing. The shrinking politically active part contrasts with the expanding service domain where loyal and neutral NGOs operate (Toepler et al., 2020). Since
these NGOs do not impose an immediate threat, empowering them not only co-opts
them into the social service apparatus but also institutionalizes regime resilience.
Therefore, government-led accreditation and certification programs allow states to
take advantage of welfare modernization, nonprofit professionalization, and charitable
resources that the society is willing to contribute.
Overall, the results indicate that the Chinese party-state has shifted its nonprofit
policy from micro-management to macro-control. A greater number of disciplined
Wang
25
civic NGOs would outweigh the loss of charitable resources that otherwise would
have gone to politically connected NGOs because of the increase of total resources for
charity. Nevertheless, these certification programs promoted standardization, which in
turn encouraged nonprofit capacity-building, and provided benchmarks for the fundraising market. In this sense, they are beneficial for the nonprofit sector and the public’s understanding of NGOs under authoritarian rule.
Conclusion
The growth of NGOs intensified the competition for nonprofit resources under
authoritarian rule. Our knowledge of NGOs’ resource acquisition, however, did not
fully catch up with the new phenomenon in the nonprofit sector where they operate.
This study is a timely examination of the dynamics between the state, nonprofits,
and society to account for multiple patterns of nonprofit development in authoritarian states. Organizational legitimacy probably used to be irrelevant when almost all
NGOs were created in a top-down manner. Nowadays, it can be responsible for
NGOs’ donation income and moderating political connections in a way that enables
civic foundations. By decoupling the separate and interactive effects of organizational legitimacy and political connections on charitable donations, this study
offered novel perspectives to reconcile explanations for fundraising in China.
Specifically, it expanded the scholarship on political connections through new variable operationalization and extended the literature on organizational legitimacy (i.e.,
voluntary accreditation and certification) and its moderating effect to the undertested authoritarian context.
This study has four limitations. First, the data were cross-sectional, so it would
be difficult to establish causality. Nor did the 1-year data allow this study to examine the effect of time lag (i.e., period a foundation has been certificated) and changes
in certification results. Future research could gather longitudinal data and consider
using interviews, surveys, and experiments to triangulate data. Surveys could
include questions that separate certain voluntary certification programs to multiple
analytical factors. Second, this article did not distinguish between institutional
donors (i.e., firms) and individual donors. Future research may consider using
regression methods on these two sources of donation separately on foundations’
legitimacy, political connections, and other organizational attributes to examine the
extent to which these two types of donors would behave differently. Third, this
study was not fully informed of the certification processes. Existing evidence seems
to acknowledge the rigorousness of these certification programs.9 Future research
may investigate the experience of NGOs that are certified or seeking certification
to test the extent to which these programs truly corroborate legitimacy. Finally,
although contemporary authoritarian regimes have exhibited similar nonprofit policy, they differ in economic and social specifics. Therefore, we should adaptively
interpret the findings and define organizational legitimacy and political connections for each authoritarian state in a way that is appropriate for its institutional
reality.
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Nonprofit and Voluntary Sector Quarterly 00(0)
Acknowledgments
I thank Dr. Beth A. Gazley, Dr. James L. Perry, Dr. Jennifer N. Brass, Dr. Jason Y. Wu, Dr.
Chao Guo, Dr. Nicolas J. Duquette, Dr. Seth M. Freedman, and other colleagues for their constructive comments. I also thank the three anonymous reviewers who provided constructive
suggestions.
Declaration of Conflicting Interests
The author(s) declared no potential conflicts of interest with respect to the research, authorship,
and/or publication of this article.
Funding
The author(s) disclosed receipt of the following financial support for the research, authorship,
and/or publication of this article: This study received funding from the Beijing Yifang
Foundation and the Zhejiang Dunhe Foundation.
Data Availability
The instructions, data, and codes that produce the findings reported in this article are available
at http://dx.doi.org/10.13140/RG.2.2.23785.98400.
ORCID iD
Qun Wang
https://orcid.org/0000-0001-7592-9824
Supplemental Material
Supplemental material for this article is available online.
Notes
1.
2.
3.
4.
5.
6.
7.
8.
See Russia at https://www.themoscowtimes.com/2018/12/13/russians-donate-5-7-billiondollars-to-charities-per-year-report-says-a63810; Turkey at https://www.tusev.org.tr/usrfiles/images/belgeler/Individual_Giving_and_Philanthropy_in_Turkey.pdf; and China in
Table 2.
See http://www.chinanews.com/gn/2013/09-22/5305391.shtml.
See an example at http://wemedia.ifeng.com/27476671/wemedia.shtml.
The Eleventh Chinese Private Enterprise Survey showed that in 2012–2013, Chinese private firms donated to both politically connected and unconnected NGOs. For more information, see https://peng.baiji.org.cn/?p=772.
See at http://finance.huanqiu.com/people/2012-07/2894862.html?agt=61.
See RICF at https://github.com/ma-ji/RICF; Wang (2018a) at http://doi.org/10.13140/
RG.2.2.35141.55525; and Wang (2018b) at https://static-content.springer.com/esm/art%3
A10.1007%2Fs41111-018-0094-2/MediaObjects/41111_2018_94_MOESM1_ESM.xlsx.
A reviewer commented that public fundraising qualification should be a proxy of organizational legitimacy variable, too. This could be so after 2016, but public fundraising qualification was not a certified qualification in 2013. See a discussion on public fundraising
qualification and analysis of this variable in the Supplemental Online Material.
I thank the reviewer who suggested adding university foundation as a control variable.
Wang
9.
27
See examples at http://www.chinadevelopmentbrief.org.cn/news-22152.html and http://
www.bnu1.org/show_1960.html.
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Author Biography
Qun Wang is an assistant professor in the Department of Political Science and Public
Administration at the University of Toledo. He holds a PhD in public policy from Indiana
University Bloomington. His research interests include government–nonprofit relations and
social innovation.