Biological Conservation 92 (2000) 359±369
www.elsevier.com/locate/biocon
Spiny lobster, Jasus edwardsii, recovery in New Zealand
marine reserves
S. Kelly a,*, D. Scott b, A.B. MacDiarmid c, R.C. Babcock a
a
University of Auckland, Leigh Marine Laboratory, PO Box 349, Warkworth, New Zealand
b
University of Auckland, Tamaki Campus, Private Bag 92019, Auckland, New Zealand
c
NIWA, PO Box 14-901, Kilbirnie, Wellington, New Zealand
Received 11 May 1998; received in revised form 27 May 1999; accepted 25 June 1999
Abstract
The abundance, size, biomass and reproductive output of spiny lobsters, Jasus edwardsii, from replicated sites nested within four
marine reserves and similar non-reserve locations in north-eastern New Zealand were compared. No time±series data were available
from three of the reserves so the ages of the reserves (3±21 years) were used to infer temporal patterns of lobster population
recovery. Linear models indicated that the mean density of the total lobster population increased 3.9 and 9.5% in shallow (<10 m
depth) and deep sites (>10 m depth), respectively, for each year in which the reserves were established, while the mean size of
lobsters was estimated to increase by 1.14 mm per year of protection. As a consequence lobster biomass (kg/500 mÿ2) was conservatively estimated to increase by 5.4% per year of protection in shallow sites and 10.9% per year of protection in the deep sites
and egg production (eggs/500 mÿ2) by 4.8 and 9.1% per year of protection for shallow and deep sites respectively. # 2000 Elsevier
Science Ltd. All rights reserved.
Keywords: Lobster; Marine reserves; Jasus edwardsii; Marine protected areas
1. Introduction
Over the last 20 years considerable attention has been
directed toward examining the role marine reserves can
have in marine conservation and ®sheries management.
The potential advantages of providing areas free from
extractive exploitation have been extensively reviewed
(Bohnsack, 1990; Roberts and Polunin, 1991, 1993;
Dugan and Davis, 1993; Jones et al., 1993; Rowley,
1994), but empirical evidence which supports proposed
bene®ts, such as allowing populations of exploited species to recover, is limited, especially from temperate
locations. Published data on the impact of temperate
marine reserves has only been obtained from a few sites
in the Mediterranean (Bell, 1983; GarciÂa-Rubies and
Zabala, 1990; Dufour et al., 1995; Harmelin et al.,
1995), South Africa (Buxton and Smale, 1989, 1991;
Bennett and Attwood, 1993), Australia (Edgar and
Barrett, 1997), and New Zealand (McCormick and
* Corresponding author.
E-mail address: casl@xtra.co.nz (S. Kelly).
Choat, 1987, Cole et al., 1990, MacDiarmid and Breen,
1993), with most attention focused on determining the
impact of protection on the biomass, size, abundance,
or species assemblages of ®sh. Results have been mixed,
with some species showing clear patterns of recovery
while others have apparently not responded to protection or researchers have failed to adequately demonstrate evidence of recovery. The failure to demonstrate
the eects of protection does not necessarily mean
populations have not responded, rather it may re¯ect
the limitations of commonly used sampling methodologies and analysis.
The ability to generalise about the eects of temperate
marine reserves has also been hampered by the use of
poorly designed surveys with inadequate levels of replication or controls (Jones et al., 1993, Rowley, 1994).
Jones et al., (1993) suggested the design of most surveys
on marine reserves failed to meet the most basic requirements for any impact study. They highlighted the fact that
most studies were confounded because they only compared a single protected location with a non-protected
control, leading to the possibility that observed dierences
were due to variability from location to location rather
0006-3207/00/$ - see front matter # 2000 Elsevier Science Ltd. All rights reserved.
PII: S0006-3207(99)00109-3
360
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
than protection eects. They were also critical of the
lack of data from the periods prior to the establishment
of most marine reserves which would have enabled
before and after comparisons to be made. Some studies
did not even attempt to provide comparisons with controls but used changes in abundance estimates within a
reserve through time as a measure of protection eects
(Bennett and Attwood 1991, 1993). Of the 11 known
published studies examining the impact of temperate
marine reserves, all concluded that protected areas
allowed the recovery of at least some species; however,
nine only looked at a single marine reserve, one compared a single site inside the reserve with two control
sites outside, six only compared one site within the protected area with one control site outside and two had no
control sites at all (Table 1). Inadequacies in sampling
design clearly mean that conclusions drawn from previous studies of temperate reserves must be treated with
a degree of caution.
We know of only one published study on temperate
marine reserves which has provided data from more
than one protected area in order to increase the degree
of generality. In a study incorporating both temporal
and spatial data MacDiarmid and Breen (1993) compared the abundance of spiny lobsters, Jasus edwardsii,
at two marine reserves with three control locations in
northeast New Zealand. Their sampling design included
replicated samples taken at a number of sites nested
within each location. However, they obtained con¯icting results with lobsters occurring in highest densities
within one reserve and lowest densities within the other.
The lack of shallow-water boulder habitat at the low
density reserve and its location in relation to the continental shelf and major currents were cited as possible
explanations for this result, highlighting the diculty of
making generalisations with limited levels of replication.
Some of the shortcomings evident in prior studies
were due to the lack of data from before the reserves
were established and the low number of reserves available for study, however, the number of marine reserves
has increased to the point where it is now possible to
improve on previous sampling regimes. Our aims were
therefore to (1) increase the number of marine reserves
examined to improve the generality of the study and (2)
to provide an estimate of the rate of lobster population
recovery within marine reserves. To do this we compared the size and abundance of lobsters at sites nested
within four marine reserves and four similar non-reserve
locations in northeast New Zealand.
Time series data were not available for three of the
marine reserves so temporal changes at individual
reserves could not be examined. Therefore a dierent
approach was adopted to examine temporal patterns of
lobster recovery. The age of the reserves ranged from 3
to 21 years. Dierences in lobster abundance, size, biomass and egg production were compared between the
reserves and non-reserve controls with the expectation
that these parameters would increase in magnitude as
the age of reserve increased. This approach allowed
tentative estimates of the rates of increase in abundance,
mean size, biomass and egg production to be made.
2. Methods
Surveys were conducted at sites within and outside
four marine protected areas (hereafter called marine
reserves or locations) on the eastern coast of North
Island, New Zealand (Fig. 1). No ®shing of any kind is
allowed in any of the protected areas which varied in
age from 3 years (Cathedral Cove Marine Reserve, and
Tuhua Marine Reserve) to 14 years (Tawharanui Marine Park) and 21 years (Leigh Marine Reserve). Sampling was strati®ed and limited to broken boulder areas
and/or fractured reef, on which Jasus edwardsii commonly occur (MacDiarmid, 1991, 1994, pers obs). All
sites were dominated by a mixture of laminarian or
fucalean kelp forests and urchin zones (Evechinus chloroticus) at shallow to intermediate depths (<15 m). In
deeper areas (>15 m) kelp and urchin density decreased
Table 1
Breakdown of the survey designs for temperate marine reserves showing the level of replication for reserve and control sites
Authors
Year
# Reserve
locations
# Control
locations
Nested
reserve sites
Nested
control sites
Habitat
types
Temporal
data
Bell
McCormick and Choat
Buxton and Smale
GarcõÂa-Rubies and Zabala
Bennet and Attwood
Cole et al.
Bennet and Attwood
MacDiarmid and Breen
Dufour et al.
Harmelin et al.
Edgar and Barrett
1983
1987
1989
1990
1991
1991
1993
1993
1995
1995
1997
1
1
1
1
1
1
1
2
1
1
4
1
1
1
2
0
1
0
4
1
1
4
1
1
1
1
2
5
2
5
1
1
1±6
1
1
1
1
0
3
0
5
1
1
2±10
2
7±10
1
3
1
1±3
1
1
2
1
1
No
No
No
No
Yes
Yes
Yes
Yes
Yes
Yes
Yes
361
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
and sponges generally became larger and more abundant.
Tuhua Marine Reserve diered from the other locations
in that it is an oshore island. At Tuhua water clarity was
substantially higher, kelp cover extended to greater
depths, and there was a more diverse range of ®sh and
algal species (Jones and Garrick, 1991).
Two reef sites were selected within each marine
reserve and two from nearby areas of coast. Within the
Leigh Marine Reserve, where there is a history of lobster research (MacDiarmid, 1987, 1991, 1994; Cole et
al., 1990, 1991; MacDiarmid, et al., 1991; MacDiarmid
and Breen, 1993, 1994), sample sites were chosen with a
random number generator from a selection of ®ve
potential reef sites scattered throughout the reserve. At
the other locations, where there was no prior knowledge
of lobster abundance, formal randomisation procedures
were not carried out. Rather, reef sites were haphazardly selected from the surface prior to diving.
Two depths (<10 and 10±25 m) were sampled at each
site to allow for seasonal changes in the depth distribution of lobsters (MacDiarmid, 1991). At each location
the size of every lobster within ®ve, 50 10 m transects
was recorded. The starting position and direction of
each transect was determined by the censor swimming
for a predetermined time in a predetermined direction.
The choice of the 50 10 m transect size was based on a
pilot study conducted by MacDiarmid (1991). He compared the precision of three dierent sized transects: 10
10 m, 25 10 m and 50 10 m, in estimating lobster
abundance within the Leigh Marine Reserve and found
it to be similar in all cases. The 50 10 m transect was
therefore selected to permit at least one transect per dive
to be completed in areas of high lobster abundance, and
limit the number of zero counts in areas of low lobster
abundance.
The visual size estimation method was used (MacDiarmid, 1991), with divers estimating carapace length
(C.L.) to within 5 mm without capturing or handling
individual lobsters. This level of accuracy was achieved
through a series of calibration dives where the size of
individual lobsters were ®rst estimated, after which each
lobster was caught by hand and measured with vernier
callipers to obtain a true length measurement. Sampling
at Tuhua, Cathedral Cove and Leigh was done by the
same censor, whereas he and two other censors sampled
Tawharanui Marine Park. An analysis of covariance
(ANCOVA) was used to test for dierences between the
Tawharanui Marine Park censors. No signi®cant dierence was found between the slopes of the relationship
between estimated and actual carapace length for each
censor (p=0.3844). However, a signi®cant dierence
was found between the intercepts (p=0.0001). Least
squares means were then calculated and pairwise comparisons using Bonferroni corrections carried out (Table
2). The range of the least squares means (2.8 mm) was
less than the 5 mm accuracy margin required by each
censor and pairwise comparisons were unable to detect
any signi®cant dierences among the censors. Therefore
the dierences detected by the ANCOVA were considered to be trivial. Where possible the sex of every
lobster was also determined visually at all sites except
those within the Leigh Marine Reserve where these data
were available from a separate study conducted in the
same month 1 year earlier (Kelly, unpublished data).
2.1. Data analysis
2.1.1. Abundance
Two features complicated the analysis of abundance
data. Firstly, the count data was not normally distributed and was skewed. Secondly, the sites within
Table 2
Pairwise comparisons and least square means obtained from carapace
length estimates for each censora
p Values of pairwise comparisons
Censor 1
Censor 2
Censor 3
Fig. 1. Map of north-eastern New Zealand showing the locations of
the four marine protected areas surveyed in the study.
a
Censor 1
±
0.4911
0.0414
LS Mean (S.E.)
Censor 2
±
±
0.1499
123.9 (0.8718)
124.4 (0.8695)
126.7 (1.0417)
Note the signi®cant p value after Bonferroni correction is 0.0167.
362
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
locations and the transects within sites were not considered to be independent. The count data were therefore transformed [ln(count +1)] and analysed using
linear mixed models which allowed for both ®xed and
random eects, and for correlations between observations. The particular software used was the function lme
developed by Pinheiro, Bates, and Lindstrom (Pinheiro
and Bates, 1995) and incorporated into the software
package S-Plus (Statistical Sciences, 1993). An accessible introduction to the software is given in Venables
and Ripley (1997, Section 10.3), and a comprehensive
discussion of the models and the modelling processes
used is given in Longford (1993).
Two sets of counts were analysed, total lobster
counts, and counts of lobsters above the legal size limit
(>100 mm C.L.). Linear mixed models were ®tted and
the signi®cance of terms in the models was tested using
likelihood ratio tests. In addition to the tests, linear
model diagnostics were used to check the model
assumptions. For each model the residuals were plotted
against ®tted values, data against ®tted values, and
normal quantile±quantile or qqplots of residuals
obtained. These plots were used to check the assumption of normally distributed errors, to check for outliers,
heteroscedasticity, or other problems. The value of the
Akaike Information Criterion (AIC) was also considered to determine the most appropriate model. The
model which had the minimum AIC was considered
optimal and represented a compromise between model
®t and complexity (Akaike 1973, 1974).
were skewed, and that a logarithmic transformation was
required. This caused problems with transects in which
no lobsters were observed, giving an estimated zero
biomass. The solution to this problem was to omit those
transects with no lobsters. This was not entirely satisfactory because it arti®cially in¯ated the mean biomass
of sites containing samples with no lobsters, thereby
introducing bias into the ®tted models. The results of
this section of the analysis should therefore only be
regarded as approximate. However, the bias was conservative and underestimated the relative eect of protection on lobster biomass, as there were fewer zero
counts in reserve than non-reserve transects (7 cf.19).
The fecundity of individual females was estimated
according to the formula given by MacDiarmid (1989)
where fecundity =0.169 CL3.0091. Using this formula
the total number of eggs produced per transect was calculated and log transformed prior to analysis. Within
the Leigh Marine Reserve MacDiarmid (1989) found
that the size at onset of maturity for female J. edwardsii
was 87.5 mm C.L. Females above 90 mm C.L. were
therefore assumed to be mature. As with biomass,
where the sex of an individual lobster was not known it
was randomly assigned for each location based on the
size-speci®c probability of being male or female.
2.1.2. Size, biomass and egg production
To examine the response of lobster size, biomass and
egg production to protection, mixed linear models that
allowed for the lack of independence between observations were again ®tted using S-Plus. Signi®cance testing
was carried out using likelihood ratio tests, and the AIC
was considered in deciding on the appropriate model.
Diagnostic plots were used to assess the validity of the
model assumptions.
Separate length±weight relationships were established
for male and female lobsters (MacDiarmid, unpublished
data) and biomass was determined by converting length
to weight after log-log transformation. Lobsters whose
sex could not be determined visually were randomly
assigned a sex based on the probability of being male or
female in a particular 10 mm C.L. size class at each
location. This method was deemed preferable to simply
assigning equal probabilities to males and females as the
size frequency distributions for the sexes varied markedly. As no sex data was collected within the Leigh
Marine Reserve, data from a survey conducted one year
earlier was used to determine the size class probabilities
and assign sexes accordingly.
In attempting to model the eect of status, depth and
age of reserve on biomass, it was found that distributions
The abundance of individual sexes was not examined
separately, rather the sex data were pooled and total
lobster counts analysed. Boxplots of the pooled data for
the total number of lobsters against status (reserve or
non-reserve), and depth (deep or shallow) showed evidence of more lobsters in the reserves compared to nonreserves, although there was one obvious outlier in the
non-reserves and some possible outliers in the reserves
(Fig. 2). A boxplot of total number of lobsters against
the age of the reserve also gave some indication of
increasing numbers with age (Fig. 3a.) and counts of
lobsters above the legal size limit (i.e. >100 mm C.L.)
showed a similar trend (Fig. 3b).
The initial model used for analysis of both the total
counts and the counts of lobsters over 100 mm incorporated ®xed eects for reserve (Cathedral Cove,
Tawharanui, Tuhua or Leigh), status (in or outside the
reserve), depth (deep or shallow) and all possible interactions between these three factors (including the threeway interaction), plus random eects for reserve and
depth and the interaction between reserve and depth.
Fitting both random and ®xed eects for particular
factors is equivalent to treating the eect of a factor as
being random with a normal distribution, but dierent
levels of the factor have distributions with dierent
3. Results
3.1. Abundance
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
363
Fig. 2. Boxplots of the raw count data comparing (a) transects from
reserve and non-reserve areas, and (b) deep and shallow sites. The
central boxes enclose data falling between the 25th and 75th percentiles, while the stems indicate the extent of data falling between the
10th and 90th percentiles. Data points falling outside these ranges are
plotted individually.
Fig. 3. Boxplots of (a) raw count data, and (b) counts of lobsters over
100 mm carapace length, from reserves of dierent ages. Data from nonreserve areas has been are pooled at age zero, and data from Cathedral
Cove and Tuhua marine reserves pooled at age 3. The central boxes
enclose data falling between the 25th and 75th percentiles, while the
stems indicate the extent of data falling between the 10th and 90th percentiles. Data points falling outside these ranges are plotted individually.
means, which are given by the ®xed eects. Considering
reserves for example, the number of lobsters was expected to vary between reserves simply because of dierences in the age of reserves. In addition to an eect due
to a reserve being a particular age, that is the ®xed
eect, the reserves may also be considered as a sample
from a population of possible reserves of the same age.
The additional variability introduced by this was modelled by including the random eect. The correlation
between transects at the various sites was taken into
account by treating transects within a given site as a
cluster, where each cluster represented observations that
were expected to be related (Pinheiro and Bates, 1995).
The ®rst step in the modelling process was to see
which random eects were needed. The results of this
procedure were dierent for the total counts compared
to the lobsters over the legal size limit. For the total
counts no random eects were necessary, while for the
counts of larger lobster, only the interaction between
reserve and depth could be eliminated. However, further
364
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
consideration of the design suggested that random
eects for reserve and for depth were appropriate and
should be included in both cases. A random eect for
reserve allowed for correlation between sites within a
reserve and also allowed the generalisation of results by
treating the reserves surveyed as a sample of possible
reserves. Similar arguments supported the inclusion of a
random eect for depth. Therefore for consistency, and
because of these design aspects, random eects for
reserve and depth were included in subsequent models
of both total lobster counts and counts of legal sized
lobsters.
In the initial phase of the analysis possible outliers
were also identi®ed. For the total count data, it was
decided to eliminate a shallow non-reserve transect at
Cathedral Cove where a very large number of small
lobsters was observed. A shallow reserve transect at
Leigh was also omitted from the analysis of larger lobsters. In this transect no lobsters were observed, while
all of the other transects at that site contained substantial numbers of lobsters. These observations were
not errors in the data, but simply re¯ected the degree of
variation present, and it was considered that their
inclusion might have lead to the model assumptions
being violated.
After deciding on outliers and random eects attention was turned to ®xed eects. A major concern of the
study was to determine the eect of age of reserve on
lobster numbers. With this aim in mind, models using
the variable ``age of reserve'' were tried, where age was
taken to be zero for the unprotected sites and equal to
the number of years the reserve had been established for
sites within each reserve. With this de®nition, knowledge
of the status of a site, and the reserve in which the site is
situated, gives knowledge of the value of ``age of reserve''.
Thus models containing the variable age of reserve were
submodels of models containing the variables status and
reserve.
The model selected by this process for both the total
counts and the counts of larger lobsters included ®xed
eects for reserve, age of reserve, and depth, plus interactions between reserve and depth, and age of reserve
and depth. For total counts in the deep sites the age of
reserve term was highly signi®cant (p <0.0001), and
gave a coecient of 0.0906, which represented the
change in ln(count +1) for each year of protection. The
exponent of this value gives the proportional increase in
the expected lobster count +1, per year of protection.
When the counts are large this is approximately equal to
the ratio of counts between consecutive years, and hence
gives the percentage increase. For the deep transects the
expected annual rate of increase was e(0.0906)=1.0948, or
approximately 9.5% per year of protection. For shallow
transects the age of reserve term was signi®cant and
gave an approximate rate of increase of 3.9% per
annum (p=0.025). The model without the interaction
between age of reserve and depth provided a less satisfactory ®t, but gave an approximate rate of increase in total
counts of 7.4% per annum (p<0.0001). The analysis of the
counts of lobsters over 100 mm in carapace length revealed
approximate rates of increase of 6.2% per annum
(p<0.0001) for deep transects and 12.2% per annum
(p<0.0001) for shallow transects. The rate of growth in
the model without interaction was 7.4% per annum
(p<0.0001).
3.2. Size
Of the 2100 lobsters counted, the sizes of 2074 were
estimated. When a lobster was not in full view a size
estimate could not be made. We judged that lobsters
whose carapace length could not be estimated did not
dier in any systematic way from to those whose sizes
were determined, so they were therefore ignored. Plots
of the size data indicated that lobsters were larger inside
the reserves than outside, and that there was a relationship between the age of the reserve and lobster size, with
the largest lobsters being found in the older reserves
(Fig. 4). However, there was no obvious dierence in
the mean size of lobsters in the two older reserves, nor
between mean sizes for the group of more recently
established reserves.
Modelling of the size data was more complicated than
the other analyses because there was an additional level
of sampling. For abundance, biomass and egg production, the response was at the transect level. For the size
data, the response was the size of individual lobsters
within transects. Transects were therefore treated as
clusters and sites as random eects to model the possible correlation between transects at the same site. A
random eect for depth was also included in the initial
model as well, but reserve and status random eects
were not included since these were confounded with site
because of the design used. Plots of the data and of
residuals from the various models examined indicated
that transformation was not necessary so the raw data
was used in this analysis. Testing of random eects
indicated that these were also unnecessary. The ®xed
eects were then examined; starting with a model
incorporating ®xed eects for reserve, status and depth,
plus all interactions. The model with the smallest AIC
had eects for reserve, age of reserve, depth, and the
interaction between depth and reserve. The age of
reserve term was highly signi®cant (p<0.0001) and
indicated an increase in average size of 1.14 mm per
year.
3.3. Biomass
Initial descriptive analysis indicated that biomass
appeared to increase in proportion to the number of
years the reserve had been established (Fig. 5a), and
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
365
Fig. 4. Size distributions of lobsters from protected and unprotected sites in and around Cathedral Cove Marine Reserve, Tuhua Marine Reserve,
Tawharanui Marine Park and Leigh Marine Reserve. Data from all of the deep and shallow sites at each location were pooled.
that greater biomass was supported in shallow water
than in deep water. Modelling was carried out using the
same procedure as for the count data with the response
being the natural log of biomass. Testing revealed no
need to incorporate random eects for reserve and
depth, and these were omitted from the model. The
selected model included ®xed eects for reserve, age of
reserve, depth and the interaction between age of reserve
and depth. The coecient for age of reserve for deep
transects was 0.103 (p<0.0001) giving an estimated
366
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
factor, and that the number of eggs produced within a
given area increased with the age of the reserve (Fig.
5b). The drop apparent in the boxplot of the 3 year old
reserves was due to lower egg production in Tuhua
Marine Reserve (Fig. 5b). Random eects for reserve
and depth were not needed, and the model selected had
the same ®xed eects as in the model for biomass. The
estimated rate of increase in egg production was determined to be 9.1% in deep transects (p<0.0001), and
4.8% in shallow transects (p=0.0009). The model without an interaction between age of reserve and depth was
acceptable and gave an overall rate of increase of 6.7%
per year (p<0.0001).
4. Discussion
Fig. 5. Boxplot of (a) biomass, and (b) egg production comparing
reserves of dierent ages. Data from non-reserve areas has been
pooled at age zero, and data from Cathedral Cove and Tuhua marine
reserves pooled at age 3. The central boxes enclose data falling
between the 25th and 75th percentiles, while the stems indicate the
extent of data falling between the 10th and 90th percentiles. Data
points falling outside these ranges are plotted individually.
increase in biomass of 10.9% per year. For shallow
transects, the rate of growth was estimated to be 5.4%
per year (p=0.003). The model without an interaction
between age of reserve and depth did not ®t particularly
well but gave a rate of increase of 8.1% per year
(p=0.0002).
3.4. Egg production
Egg production was modelled in a similar fashion to
biomass. Plots of the natural logarithm of egg production indicated that depth might not be an important
This is the ®rst published study to demonstrate
population level responses to protection at more than
one temperate marine reserve. Inconclusive results and
the examination of single marine reserves has meant
that previous studies were unable to generalise to other
areas (Bell, 1983; McCormick and Choat, 1987; Buxton
and Smale, 1989; GarciÂa-Rubies and Zabala, 1990; Cole
et al., 1990; Bennett and Attwood, 1991, 1993; MacDiarmid and Breen, 1993; Dufour et al., 1995; Harmelin
et al., 1995). In our study the use of several marine
reserves and the inclusion of a temporal component
strengthens the level of con®dence with which we can
make large scale inferences about the response of lobsters to protection from ®shing.
Lobster biomass was higher within the protected
zones than in unprotected areas, with the dierence
estimated to increase by 5.4 to 10.9% per year depending on depth. As transects with no lobsters were omitted
from the analysis, and the unprotected sites had more
transects with zero counts, this estimate is considered to
be conservative. The increase in biomass was due to an
increase in both the size and abundance of lobsters
within the protected zones. These results demonstrate
the potential of marine reserves to allow populations to
recover, but they also illustrate the heavy impact ®shing
has on lobster populations.
The inclusion of reserves of dierent ages allowed an
indirect measure of the rate of population recovery. The
data indicate that protected lobster populations could
increase in abundance by 3.9% per annum in shallow
sites and 9.5% per annum in deeper sites. However
these estimates were based on data from only four
reserves. The relatively low level of replication does not
provide a good measure of inter-site variability; so
model parameters derived from it must be treated cautiously. For example, marked dierences were found in
the recovery patterns of the two 3 year old reserves.
Many factors may in¯uence recovery rates at individual
sites and contribute to variability. For instance, recruit
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
supply and juvenile survivorship may vary from place to
place and over time (Booth, 1994; Briones-Fourzan,
1994; Butler et al., 1997; Gosselin and Qian, 1997; Hunt
and Scheibling, 1997; Wahle and Incze, 1997). Ultimately, population growth may be limited by the ecological suitability of a particular site or the carrying
capacity of an area (Bologna and Steneck, 1993; Parrish
and Polovina, 1994). However, comparison with the
results presented by MacDiarmid and Breen (1993)
suggest that lobster populations can respond rapidly to
protection and that our estimates of the rate of population recovery may be conservative. MacDiarmid and
Breen (1993) examined the abundance of lobsters in
shallow sites of less than 10 m within the Leigh Marine
Reserve and found that overall, mean densities ranged
from 10.07 lobsters per 100 m2 in March/April 1985 to
6.08 lobsters per 100 m2 in July/August 1985. Converting our density data to the same unit area gave values
for the Leigh Marine Reserve of 5.89 lobsters per 100
m2 which is below either of their estimates. This suggests that lobster densities within the Leigh Marine
Reserve reached very high levels within 8 years of its
establishment and have since declined. A number of
factors limit the validity of making such direct comparisons with our study. For instance MacDiarmid and
Breen (1993) sampled from dierent sites within the
reserve, conducted their survey at dierent times of
year, used dierent sampling unit sizes, and limited their
sampling to a single depth strata. Nevertheless, the fact
that the abundances they reported were substantially
higher than any found in our study supports their
assertion that recovery within the Leigh Marine Reserve
occurred rapidly.
Given that marine reserves allow J. edwardsii populations to recover it seems prudent to examine the role
they could play in the management of this species. There
are a number of possible bene®ts in providing areas free
from ®shing pressure. Roberts and Polunin (1993) proposed that adults within marine reserves may help
restock unprotected areas through the export of larvae
and recruits. As egg production increases exponentially
with body length (Roberts and Polunin 1991, 1993), and
there are more, larger, egg producing adults within
marine reserves, the contribution of protected areas to
overall egg production should exceed the ratio of protected area to ®shing grounds. Our comparisons of egg
production within the reserves and non-reserve areas
support this assertion. However, it is more dicult to
determine what, if any impact increased egg production
would have on recruitment levels, as stock±recruitment
relationships are notoriously dicult to demonstrate
(Caddy, 1986; Caputi, 1993). In fact there is even some
debate as to whether recruitment is related to stock size
at all, except at extremely low levels of egg production
(Koslow, 1992; Myers and Barrowman, 1996; Francis,
1997; Gilbert, 1997; Hillborn, 1997; Myers, 1997). This
367
is particularly so in species like J. edwardsii whose free
swimming larval life span may range from 12 to 24
months (Booth and Phillips, 1994). Because of the poor
relationship between spawning stock and recruitment,
marine reserves should only play a signi®cant role in
maintaining or enhancing recruitment in unprotected
areas when stock sizes in those areas are severely
depleted (Roberts and Polunin, 1991). Although
potentially serious reductions in J. edwardsii stocks
have occurred in some New Zealand management
areas, current management strategies are considered
sucient to allow them to rebuild (Annala and Sullivan, 1996; Breen and Kendrick, 1997). However, problems with conventional ®sheries management
techniques (e.g. Hofmann and Powell, 1998) have led
directly to the promotion of marine reserves as insurance against poor management, stock depletion and
ultimately recruitment failure. A system of marine
reserves may therefore be a prudent management strategy to ensure that adequate spawner biomass is maintained in J. edwardsii stocks.
Marine reserves have also been attributed with having
the potential to maintain or enhance the yield of adjacent ®sheries (Alcala and Russ, 1990; Kelly, 1999). As
populations build up within marine reserves food or
habitat requirements may eventually limit further
population expansion. Mobile species can respond by
emigrating to unprotected areas were there is less pressure on resources, and in the process become susceptible
to capture. Alternatively individuals may leave protected areas through general diusive or migratory
movements (Kelly, 1999). Alcala and Russ (1990) proposed that ®shing yields adjacent to the Sumilon Marine
Reserve in the Philippines were enhanced by such processes. They found that when ®shing was re-established
within the reserve the total yield around Sumilon Island
declined by 54%, despite a larger area of reef being
®shed (i.e. both the reserve and non-reserve areas).
However, modelling suggests that the establishment of
marine reserves will in most cases lead to a reduction in
the yield of ®sh stocks (Polacheck, 1990; DeMartini,
1993; Attwood and Bennett, 1995). Only under conditions of heavy ®shing mortality and moderate rates of
transfer were small increases in yield predicted. Nevertheless, intensive trapping for lobsters occurs around the
boundaries of at least three of the marine reserves surveyed in this study, and the boundaries of all the
reserves are popular dive sites for SCUBA divers hunting for lobsters. The popularity of these areas for
catching both lobsters and ®n-®sh suggests that there is
a public perception that reserves contribute to the local
®shery. This perception is backed up by the commercial
catch rates of lobsters obtained around the boundary of
the Leigh Marine Reserve which show strong seasonal
variability but are relatively high compared with areas
remote from the reserve (Kelly, 1999).
368
S. Kelly et al. / Biological Conservation 92 (2000) 359±369
While direct bene®ts to lobster management remain
unclear, areas of zero exploitation can be used to obtain
valuable information for ®sheries research and management. The recovery of lobsters within marine reserves
has provided ecologists with the opportunity to work on
relatively natural populations free from human interference. As a result marine reserves have made a substantial contribution to our understanding of J.
edwardsii ecology (MacDiarmid, 1987, 1991, 1994;
MacDiarmid et al., 1991,; Kelly, 1999; Kelly et al., 1999)
and may permit more eective management strategies to
be developed.
Acknowledgements
This research was funded by the Department of Conservation and the Graduate Research in Industry Fellowship Scheme. Additional support was provided by
Leigh Fisheries, University of Auckland, Bay of Plenty
Polytech, Leigh Marine Laboratory, Keith Gregor, Gilli
Adams, Peter Carter, Andy Garrick, Alan Jones and
Rawiri Tuawau. We would also like to thank all of the
students and research assistants who helped with the
®eld work.
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