Changes in habitat specificity of species at their climatic range boundaries
Transcript of Changes in habitat specificity of species at their climatic range boundaries
L E T T E RChanges in habitat specificity of species at their
climatic range boundaries
Tom Oliver,1* Jane K. Hill,2 Chris
D. Thomas,2 Tom Brereton3 and
David B. Roy1
1NERC Centre for Ecology &
Hydrology, Maclean Building,
Benson Lane, Crowmarsh
Gifford, Oxfordshire OX19 8BB,
UK2Department of Biology (Area
18), University of York, PO Box
373, York YO10 5YW, UK3Butterfly Conservation, Manor
Yard, East Lulworth, Wareham,
Dorset BH20 5QP, UK
*Correspondence:
E-mail: [email protected]
Abstract
Species are thought to have more restricted niches towards their range boundaries,
although this has rarely been quantified systematically. We analysed transect data for 41
butterfly species along climatic gradients within Britain and show that 71% of species
have broader niches at sites with milder winters. Shifts in habitat associations are
considerable across most species� ranges; averaged across all 41 species, we estimate
that if 26% of individuals were associated with the favoured habitat on the species�warmest transect, then 70% of individuals would be confined to this habitat on the
species� coldest transect. Species with more southerly distributions in Britain showed
the greatest changes in their habitat associations. We conclude that geographic
variation in realized niche breadth is common and relatively large, especially near range
boundaries, and should be taken into account in conserving species under changing
climates.
Keywords
Bioclimatic envelope model, butterfly habitat management, habitat associations, niche
breadth, range margin.
Ecology Letters (2009) 12: 1091–1102
I N T R O D U C T I O N
Many animal and plant species have responded to recent
climate warming (Parmesan & Yohe 2003; Root et al. 2003).
Most studies of the responses of species to climate have
focused on changes in the phenology and distributions of
species (Walther et al. 2002; Thomas et al. 2006), and possible
climate-driven changes in the habitat associations of species
have largely been ignored. For example, most species
distribution models operate under the assumption of niche
conservatism (Guisan & Zimmermann 2000). However, this
may not be the case and such changes need to be incorporated
into conservation management plans and need to be
accounted for when projecting distribution changes.
Changes in species� associations with habitat will affect
the extent of suitable breeding habitat, and thus affect both
the ability of species to survive in existing parts of their
ranges, as well as the ability of species to occupy new,
climatically-suitable areas in future. Recent information for a
small number of species suggests that changes in species�habitat associations are taking place (Thomas et al. 2001;
Davies et al. 2006), although data on the generality, extent
and direction (i.e. wider or narrower habitat associations
with warmer climate) of such changes are lacking. System-
atic multi-species studies of patterns of geographic variation
in habitat associations are needed to evaluate the extent to
which these patterns may be influenced by climate.
The physical environment is important in determining
the association of species with particular habitats, partic-
ularly at the edges of their ranges (Brown 1984; Thomas
et al. 1999; Lennon et al. 2002). At the high-latitude leading
edge boundaries of species� ranges, populations may
become restricted to particular habitats. This may be due
to these habitats having especially warm microclimates
(thus increasing the chances of species completing their life
cycles, and ⁄ or increasing survival and fecundity), or
because these habitats support high population growth
for other reasons (e.g. habitats with high resource
availability), enabling populations to persist despite
increased climate-related mortality at range margins. By
contrast, in the centre of species� ranges, a relatively wide
range of locations and habitats are likely to meet the
species� requirements for growth and survival. It is also
possible that because local abundances tend to be greater
towards the centre of ranges (Brown 1984), increased
density dependence in the core habitats in these areas may
Ecology Letters, (2009) 12: 1091–1102 doi: 10.1111/j.1461-0248.2009.01367.x
� 2009 Blackwell Publishing Ltd/CNRS
lead to increased use of a wider range of subordinate
habitats.
Changes in species� habitat associations have been
recognized in certain cases (Lennon et al. 2002; Davies
et al. 2006; Schofield et al. 2009). However, information on
the generality and causes of such patterns are required
because spatial and temporal variation in climate-driven
species� habitat associations will have important implica-
tions for developing appropriate management plans under
changing climates. It is possible that the greatest immediate
need for conservation management responses to climate
change will relate to species� habitat changes. First,
prescriptions for habitat management to maximize num-
bers of individuals may need to recognize that spatial
variation in habitat use exists, such that management varies
from one location to another within a species� range.
Second, climate change may modify species� habitat
associations in a given location over time, such that
current static habitat management prescriptions could
become inappropriate, and possibly detrimental, in the
longer term. Third, predicting range shifts of species under
future climate change requires understanding of climate–
habitat interactions. This has special relevance at leading
edge expanding range margins, where habitat availability
may be a major determinant of range expansion (Hill et al.
2001; Wilson et al. 2009), and at trailing range edges where
species may become increasingly confined to core habitats.
However, there is currently insufficient information on the
generality of climate-driven shifts in habitat associations to
inform adaptation strategies.
Here we analyse data for 41 species of southerly-
distributed British butterflies, and examine the degree to
which species� habitat associations change spatially across
Britain, in relation to climate. For each species, we analyse
abundance data from line transects (Pollard & Yates 1993)
to estimate the proportions of individuals associated with
different habitat types in different parts of Britain, and we
relate these changes to spatial variation in climate. Our study
species have the cores of their British distributions in
relatively warm southern regions of Britain (and also occur
further south within Europe), and so we predict that habitat
associations will become increasingly constrained towards
species� leading edge (cool) range limits. We also carry out a
multispecies analysis to test whether the locations of species��cold� range limits in Britain affect the degree to which niche
breadth varies across climate space. If climate limits species�habitat use, then we may expect habitat associations to
become rapidly constrained towards range edges as climatic
suitability tails off to zero. Therefore, we predict that species
with more southerly distributions, and therefore occupying
more marginal areas of their range in Britain, will show the
greatest rate of change in habitat associations across climate
space. Finally, we illustrate the implications of our results for
projecting species� range expansions by mapping variation in
niche breadth of an expanding species across its geograph-
ical range in Britain.
M A T E R I A L A N D M E T H O D S
Data sources
Butterfly abundance data were derived from the United
Kingdom Butterfly Monitoring Scheme (UKBMS) transect
surveys. Full details of the UKBMS scheme can be found in
Pollard & Yates (1993), but we briefly outline them here.
Transects are 5 m wide, between 0.5 and 7 km in length and
each transect is subdivided into sections of 10–2000 m,
corresponding to 12 habitat types. For all British species, the
numbers of butterflies in each section of a transect are
recorded weekly from April to September, when prescribed
weather conditions are met. In this study, we analysed all
butterfly transects that were recorded between 1976 and
2007 [mean duration of records at each transect loca-
tion = 14.4 years ± 0.8 (SE)], for which habitat types of all
sections were known and for which more than one habitat
type was present on the transect. In total we analysed 117
transects which were distributed across Britain (Fig. 1).
Although the duration of recording varied among transects,
there was no significant pattern with spatial climate
(accumulated temperatures above 5 �C) for the first or last
Figure 1 Locations of the 117 United Kingdom Butterfly Moni-
toring Scheme transects used for the analysis.
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year that a transect was recorded, nor the total duration of
recording (regression of first year of recording on mean
growing degree days above 5 �C at each site :
F1,115 = 0.339, P = 0.562; last year: F1,115 = 0.438,
P = 0.509; duration: F1,115 = 0.549, P = 0.460), and so
data were summed over all years to produce a single
measure of habitat specificity for each species for each
transect (see below). We were interested in spatial patterns
of habitat association and so we omitted from analysis
species that occurred on fewer than five transects, because
regressions with so few data points are likely to have very
large errors. This resulted in 41 southerly-distributed species
available for analysis (Table 1).
Climate data were obtained from CRU ts2.1 (Mitchell &
Jones 2005) and CRU 61–90 climate (New et al. 1999)
datasets and interpolated to the 10 km GB Ordnance
Survey grid.
We used three bioclimate variables that are known to
affect butterfly physiology and distribution: growing degree
days above 5 �C (GDD5), mean daily temperature of the
coldest month (MTCO) and the ratio of actual to potential
evapotranspiration (APET) (Warren et al. 2001; Hill et al.
2002). For each transect location, each climate variable was
computed as the mean of a 10-year period between 1989
and 1999 for the 10 km grid square containing the transect.
Measures of habitat specificity
To assess spatial variation in habitat associations we first
quantified the habitat specificity of each species (at each site)
in relation to its most favoured habitat (Pobs, see below). We
defined most �favoured habitat� as the habitat type which
most frequently had the highest density of butterflies of that
species across all 117 transects; and �subordinate� habitat as
all other habitats present on transects with lower densities of
that species (including zero density). �Subordinate� habitat
was treated as a single entity; summing section lengths and
butterfly counts for the different non-favoured habitat types
on a given transect. Any transect that did not contain both
favoured (for a given species) and subordinate habitat types
was subsequently omitted from analysis for that species,
giving the mean number of transects analysed per species as
51.2 ± 4.9 (SE). We first standardized our analyses to
account for different areas of habitat within transect routes
by dividing butterfly abundance by habitat area to give
butterfly densities per km2 for each species in favoured and
subordinate habitat types. For each species, the ratio of the
density of butterflies in the favoured habitat to the density
of butterflies in the subordinate habitat was then expressed
as a proportion, following eqn 1. This value (Pobs)
represents the expected proportion of individuals in the
favoured habitat if all habitat types were of equal area, as
follows:
Pobs ¼na
ðnaþ m
bÞ ð1Þ
Pobs = proportional relative density of butterflies in the
favoured habitat
a = area of transect route containing the favoured
habitat (km2)
b = area of transect route containing subordinate
habitat (km2)
n = total number of butterflies in the favoured habitat
m = total number of butterflies in the subordinate
habitat
For each species, we carried out logistic regression on the
observed proportional relative densities (Pobs) across all
transects occupied by the species, to estimate how the
expected proportion of individuals in the favoured habitat,
termed pi, varied with climate. Sample sizes for each transect
were the total number of butterflies observed on the
transect in both favoured and subordinate habitats. By
assessing habitat use in this way by using proportional values
(i.e. rather than using raw count data), we minimize
problems caused by sampling effects, such as differences
in total butterfly abundance among transects, and differ-
ences in the area of available habitats on different transects
(Garshelis 2000; Manly et al. 2003).
Statistical analysis
Spatial variation in habitat specificity
We analysed spatial variation in habitat specificity for each
species across the UK using logistic regression. The aim of
our analysis was to examine how expected habitat specificity
on transect i (pi) varied with each of the three bioclimate
variables (GDD5, MTCO and APET) for the 10 km grid
square containing that transect. Some of the bioclimate
variables were strongly correlated (e.g. Pearson�s correlation
coefficient of GDD5 and MTCO was 0.85); therefore we
included each bioclimate variable in a separate logistic
regression model. Although models containing multiple
correlated explanatory variables can still produce fairly
robust predictions (hence their use in much bioclimate
envelope modelling), extracting individual variable coeffi-
cients can give misleading results. In our case, we were
interested in the individual bioclimate variable coefficients
that indicate the effect of each bioclimate variable on
species� habitat associations, so we fitted each bioclimate
variable in a separate model. For example, the effect of the
GDD5 on habitat specificity is reflected in the sign and
magnitude of the coefficient b in eqn 2. A negative
coefficient indicates that the proportion of individuals in the
favoured habitat decreases with increased GDD5 at a site.
Similarly, the effect of the MTCO on habitat specificity is
Letter Changing habitat specificity at range boundaries 1093
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Table 1 Butterfly species used in the analysis and their relationships between habitat specificity and climate
Species FH SH1 SH2 RL b c d
Aglais urticae G (0.49) HeMo DW 1124 0.0004 0.109 )1.246
Anthocaris cardamines HeMo (0.39) G DW 929 0.0002 0.105 2.681
Aphantopus hyperantus G (0.42) HeMo DW 859 )0.0016* )0.055 6.860*
Argynnis aglaja G (0.62) HeMo DW 976 )0.0024 )0.881* 19.431*
Argynnis paphia G (0.39) DW HeMo 567 )0.0032 )0.452 15.647*
Aricia agestis G (0.57) DW HeMo 483 0.0009 0.749* 3.441
Boloria euphrosyne DW (0.44) G HeMo 895 0.0001 0.286 8.182
Boloria selene G (0.54) DW Br 939 0.0026 0.611 )12.009
Callophrys rubi G (0.53) HeMo DW 905 0.0010 0.319 1.658
Carterocephalus palaemon G (0.67) HeMo DW 860 )0.0016 )0.498 8.378
Celastrina argiolus HeMo (0.42) G DW 592 )0.0009 )0.383* )1.304
Coenonympha pamphilus G (0.62) HeMo H 956 )0.0008 )0.307 4.867
Colias croceus G (0.62) HeMo DW 894 )0.0010 )0.300 5.504
Cupido minimus G (0.72) HeMo DW 915 )0.0017 )0.025 11.810
Euphydryas aurinia G (0.57) DW H 744 0.0048 )0.177 )36.789*
Gonepteryx rhamni HeMo (0.43) G DW 579 )0.0013 0.044 4.318*
Hamearis lucina G (0.66) HeMo DW 465 )0.0026 )0.271 )1.997
Hesperia comma G (0.88) H HeMo 192 )0.0284* )11.395* 77.967
Hipparchia semele G (0.44) H DW 911 )0.0183 )4.597 57.986*
Inachis io G (0.38) HeMo DW 1166 0.0010* 0.188 )3.646*
Leptidea sinapis G (0.56) DW A 567 0.0118 )1.018 )17.446
Limenitis camilla G (0.35) DW HeMo 385 )0.0023 )0.217 1.300
Lycaena phlaeas G (0.54) HeMo DW 977 )0.0014* )0.384* 6.201*
Maniola jurtina G (0.55) HeMo DW 1018 )0.0007 )0.294* 1.905
Melanargia galathea G (0.60) HeMo DW 503 0.0002 )0.113 1.266
Neozephyrus quercus DW (0.44) G HeMo 742 0.0015 0.655 0.578
Ochlodes venata G (0.46) HeMo DW 637 )0.0010 )0.432* 2.837
Pararge aegeria DW (0.50) HeMo G 938 0.0011 )0.001 )3.487
Pieris brassicae HeMo (0.38) G DW 1194 )0.0001 )0.056 )1.836
Pieris napi HeMo (0.40) G DW 1029 0.0004 0.080 )2.402
Pieris rapae G (0.40) HeMo DW 974 0.0000 )0.013 0.476
Plebeius argus H (0.69) G C 378 )0.0662 )2.163 )143.79
Polygonum c-album HeMo (0.42) DW G 708 )0.0002 )0.034 )1.868
Polyommatus coridon G (0.77) HeMo DW 277 0.0016 0.407 1.127
Polyommatus icarus G (0.58) HeMo DW 1035 0.0001 )0.078 )0.640
Pyrgus malvae G (0.58) HeMo DW 400 )0.0031 )0.019 11.448
Pyronia tithonus G (0.45) HeMo DW 564 )0.0015 )0.452* 2.127
Lasiommata megara G (0.45) HeMo DW 656 )0.0010 )0.261 4.632
Thymelicus sylvestris G (0.53) HeMo DW 607 )0.0015 )0.521* 5.950*
Vanessa atalanta HeMo (0.39) G DW 1197 0.0004 0.057 )0.968
Vanessa cardui G (0.49) HeMo UG 1198 )0.0003 )0.128 3.646
Habitat category codes for favoured habitats (FH) and the two most common subordinate habitats (SH1 and SH2) are as follows:
Br, bracken, DW, deciduous woodland, G, grassland, H, heathland, HeMo, hedgerow and mosaic habitats. The number in brackets after the
favoured habitat type refers to the proportional relative density of butterflies found in this habitat averaged across the UK, i.e. it is a measure
of habitat specificity that ranges from zero to one, with one indicating all individuals are found in the favoured habitat. Range limits of species
in Britain (RL) are the mean northing (in km) of the 10 most northerly records of a species from the UKBMS database. The relationship
between habitat specificity and GDD5 is reflected in the species� b coefficient. Negative values indicate species become less specific in
warmer locations. The relationship between habitat specificity and MTCO is reflected in species� c coefficients. Negative values indicate
species become less specific in locations with warmer winters. The relationship between habitat specificity and APET is reflected in the
species� d coefficient. Positive values indicate species become more specific in wetter sites. Values of b, c or d coefficients in bold indicate
which climate variable best explains habitat specificity for the species. Authorities for scientific names and vernacular names and are detailed
in Asher et al. (2001).
*Species with significant correlations of each bioclimate variable with habitat specificity (P < 0.05).
1094 T. Oliver et al. Letter
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reflected in the sign and magnitude of the coefficient c in
eqn 3, and the effect of the APET on habitat specificity is
reflected in the sign and magnitude of the coefficient d in
eqn 4. In each model, we also included each species� mean
yearly total abundance at a site (Ni), the number of habitat
types on transects (Hi) and the proportion of each species�favoured habitat (Fi) as control variables, because we were
interested in the effects of climate on habitat specificity
independent of these factors. There was no significant
relationship between the number of habitat types on
transects and any of the three bioclimate variables. Similarly,
there was no significant relationship between the proportion
of each habitat type on transects and any of the three
bioclimate variables (Table S1). Thus, any trends of
increased habitat specificity in marginal climates were
unlikely to be caused by underlying spatial bias in the
numbers, or proportions, of habitat types on transects.
Including these factors as control explanatory variables,
however, allowed more residual spatial variation in butterfly
habitat specificity to be explained, thereby increasing the
sensitivity of the model to detect the importance of climate
on butterfly habitat use. We tested the residuals of all three
models (eqns 2–4) for spatial autocorrelation by calculating
Moran�s I and assessing the significance of the standard
deviate (Table S2). In no cases did residuals show significant
spatial autocorrelation and thus we are confident that non-
independence of local response values is not a problem.
Finally, for each species we examined deviance of each of
the logistic regression models (eqns 2–4), to ascertain which
climate variable best explained spatial variation in habitat
associations. All three models had been fitted to the same
variable and there were no missing values in the explanatory
variables, so in all three cases the full (saturated) model was
the same, and the null model was the same. Therefore, we
sought the bioclimatic variable that provided the greatest
change in deviance relative to the null model, an approach
equivalent to a standard likelihood ratio test.
logitð piÞ ¼ aþ bGDD5i þ h1Ni þ h2Hi þ h3Fi ð2Þ
logitð piÞ ¼ aþ cMTCOi þ h4Ni þ h5Hi þ h6Fi ð3Þ
logitð piÞ ¼ aþ dAPETi þ h7Ni þ h8Hi þ h9Fi ð4Þ
Statistical analyses were carried out using the program R (R
Development Core Team 2007) version 2.7.1, using
generalized linear models (Faraway 2006). In many cases,
models were overdispersed, as indicated by the residual
standard error exceeding the degrees of freedom, therefore
�quasibinomial� errors were specified (Faraway 2006; Craw-
ley 2007). To test whether variation in each climate variable
affected butterfly habitat specificity (pi) across species, we
carried out a binomial test on the number of positive versus
negative slopes (b, c or d coefficients) which were
significantly different from zero. We also carried out a
Wilcoxon signed rank test on all slope values to see if they
differed significantly from zero.
Location of species� range limits
We tested whether the latitude of a species� leading edge
�cold� range limit within the UK affected the relationship
between habitat specificity (pi) and climate (GDD5, MTCO
or APET). Range limit was defined as the mean northing (in
km) of the ten most northerly British records of a species
from the BNM (Butterflies for the New Millenium) database
which contains species� presences at 10 km resolution from
1995 to 2004 (Asher et al. 2001; Hickling et al. 2006).
Phylogenetic autocorrelation in the response and explana-
tory variables was tested using the Moran�s I-test with Geary
randomizations (1000 iterations) using the �ape� package in
the program R (Paradis 2006; Dray & Dufour 2007). This
autocorrelative approach to test for the importance of
phylogenetic non-independence introduced by Gittleman &
Kot (1990) is preferable to automatically correcting for
phylogeny. If there is no evidence for phylogenetic
autocorrelation in either the response variable, explanatory
variables or in the model residuals, then phylogenetic
corrections (which can increase type II (false-negative) error
rates), are unnecessary (Kunin 2008). We used a butterfly
phylogeny from Cowley et al. (2001) with branch lengths
assigned using Grafen�s (1989) method.
R E S U L T S
Spatial variation in habitat specificity
Species varied considerably in their habitat specificity. For
example, the proportion of butterflies in the favoured
habitat, averaged across all the sites occupied by a species,
ranged from 0.35 to 0.88 (Table 1). In addition, within any
species there was considerable variation in habitat specificity
across sites, and the degree of habitat specificity was often
associated with the site�s climate. The majority of species
showed negative relationships between MTCO and habitat
specificity (29 of 41 species; Wilcoxon signed-rank test on
slope values: V = 247, n = 41, P = 0.0166). Of the
significant regression slopes between MTCO and habitat
specificity, eight were negative and one was positive
(Fig. 2b; two-tailed binomial test, 8 ⁄ 9 significant slopes
negative, P = 0.039). This suggests that species tend to
become more constrained to their favoured habitats in
locations with colder winters. Nevertheless, some species
showed the opposite trend and became less constrained in
cooler locations.
With regards to APET, the majority of species showed
positive relationships between APET and habitat specificity
Letter Changing habitat specificity at range boundaries 1095
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(27 of 41 species; Wilcoxon signed rank test on slope values:
V = 595, n = 41, P = 0.033). Of the significant regression
slopes between APET and habitat specificity, seven were
positive and two were negative (Fig. 2c; two-tailed binomial
test, 7 ⁄ 9 significant slopes positive, P = 0.18).
Finally, the majority of species showed negative relation-
ships between GDD5 and habitat specificity (24 of 41
species). However, these values were not significantly
different from zero, although values were approaching
significance (Wilcoxon signed rank test on slope values:
V = 282, n = 41, P = 0.054). Of the significant regression
slopes between GDD5 and habitat specificity, three were
negative and one was positive (Fig. 2a; two-tailed binomial
test, 3 ⁄ 4 significant slopes negative, P = 0.63).
To ascertain which of the three bioclimate variables
best explained spatial variation in habitat associations, we
compared the deviance of each of the logistic regression
models (eqns 2–4). The most important bioclimate
variable was APET which best explained spatial variation
in habitat associations for 20 species (Table 1). The next
best was MTCO (13 species), followed by GDD5 (eight
species).
Across all 41 species, the mean difference in habitat
specificity between sites with the coldest and warmest
winters (MTCO) in the proportion of butterflies in their
favoured habitat was 0.44 ± 0.04 (n = 41; range = 0–1).
For example, we calculate that a species with 70% of
individuals in the favoured habitat on the species� coldest
transect would have only 26% of individuals in the favoured
habitat on the species� warmest transect. Thus, there are
considerable shifts in habitat associations across most
species� ranges.
Species� abundance was also included in our logistic
regression models because we were interested in effects of
climate that were independent of changes in abundance.
There were significant effects of abundance on species�habitat associations (11 species showed significant effects of
abundance on habitat specificity in GDD5 models, eight
species in MTCO models and 11 species in APET models).
Comparing across species, however, revealed that the effects
of abundance were often in opposite directions. Thus, in
some species increasing abundance led to increased spec-
ificity, whilst in other species increasing abundance led to
decreased specificity [two-tailed binomial test to determine
if there was a consistent trend in the sign of significant
abundance slopes: GDD5 model: 4 ⁄ 11 abundance slopes
negative, P = 0.55; MTCO model: 2 ⁄ 6 abundance
slopes negative, P = 0.29; APET model: 4 ⁄ 11abundance
slopes negative, P = 0.55; Wilcoxon signed rank test on all
abundance slope values (n = 41): GDD5 model: V = 496
P = 0.40, MTCO model: V = 518 P = 0.26, APET model:
V = 530 P = 0.20]. Thus, abundance was unable to explain
the consistent spatial trend in habitat specificity shown
across species (i.e. that habitat specificity tended to be lower
in warmer and drier places with warmer winters).
Mapping habitat specificity
To illustrate the implications of our results we mapped the
changes in niche breadth of an expanding species, the
gatekeeper butterfly Pyronia tithonus L., across its geographi-
cal range in Britain. Abundance and habitat availability data
for the butterfly across Britain were unavailable at 10 km
resolution, and so we used a logistic regression model
Increased specificity in cooler sites
Increasedspecificity inwarmer sites
Increased specificity with colder winters
Increased specificity with warmer winters
Increased specificity in drier sites
Increasedspecificity inwetter sites
(b) (c)
Species' GDD5 β coefficient
Fre
qu
ency
–0.06 –0.04 –0.02 0.00 0.02
05
1015
2025 (a)
Species' APET δ coefficient
Fre
quen
cy
–150 –100 –50 0 50
05
1015
2025
30
Species' MTCO γ coefficient
Fre
quen
cy
–12 –10 –8 –6 –4 –2 0 2
05
1015
2025
30
Figure 2 Frequency distribution of b, c and d coefficients for relationships between (a) GDD5, (b) MTCO and (c) APET, and butterfly
habitat specificity (n = 41 species). The dashed vertical line at zero represents no change in specificity. The negative distribution in panel (a)
indicates that specificity of association with favoured habitats declines in warmer places. The negative distribution in panel (b) indicates that
specificity of association with favoured habitats declines in places with warmer winters. The positive distribution in panel (c) indicates that
specificity of association with favoured habitats increases in wetter locations.
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including the three bioclimate variables (GDD5, MTCO and
APET) to project changes in the habitat specificity of this
species across Britain (Fig. 3). In the example shown, the
majority of individuals of P. tithonus are restricted to
grasslands in colder and wetter parts of the range, but
butterflies are much more evenly distributed across a range
of other habitat types, such as hedgerows, deciduous
woodland and heathland, in milder coastal regions and in
the south of Britain. As this species expands its range
northwards, colonists in cool northern locations are likely to
be concentrated in grassland habitats which will reduce
expansion rates compared with warmer locations where a
wider range of habitats are utilized.
Species� range limit effects
We tested whether the location of the leading edge northern
range limit in Britain of each of the 41 southerly-distributed
butterfly species was a significant predictor of the gradient
of change in habitat specificity with climate. There was no
evidence of phylogenetic autocorrelation in the response
variable, explanatory variables or in model residuals (1000
iterations of Geary randomization of Moran�s I test for
phylogenetic autocorrelation: range limit P = 0.95, GDD5
P = 46, MTCO P = 0.84, APET P = 0.73, range limit-
GDD5 residuals P = 0.88, range limit-MTCO residuals
P = 0.90, range limit-APET residuals P = 0.95), so we used
conventional regression including data for each species as an
independent data point (Kunin 2008). We found a signif-
icant effect of species� range limit on the relationship
between GDD5 and habitat specificity, such that species
with more southerly leading edge range limits in Britain
tended to have steeper negative relationships between
GDD5 and habitat specificity (i.e. more specific to favoured
habitats in colder places) (Fig. 4a; regression of range limit
location on GDD5 b coefficient, for all 41 species:
F1,39 = 4.81, P = 0.034). We repeated the analysis for only
those 50% of species that had the most reliable slope
estimates (i.e. lowest standard errors of slope estimates) and
the trend between GDD5 and habitat specificity was even
stronger (Fig. 4d; regression of range limit location on
GDD5 b coefficient for 21 species: F1,19 = 14.07,
P = 0.001). In this case, it was apparent that species with
more northerly range limits tended to have less steep, more
positive relationships (i.e. more specific to favoured habitats
in warmer places).
Similarly for MTCO, there was also a positive relationship
between species� range limit location and the habitat
specificity-climate coefficient, such that more southerly
distributed butterflies were more specific to favoured
habitats in places with colder winters (Fig. 4b; regression
of range limit location on MTCO c coefficient for all 41
species: F1,39 = 5.237, P = 0.028; Fig. 4e; regression of
range limit location on MTCO c coefficient for 21 species:
F1,19 = 8.22, P = 0.010). Once again, slopes for more
southerly distributed species were steeper, indicating greater
rates of change in habitat specificity across climate space.
For the bioclimate variable APET, there was no
significant effect of location of species� range limit on the
relationship between APET and habitat specificity across all
41 study species (Fig. 4c; APET d coefficient-range limit
location regression; F1,40 = 0.145, P = 0.705). When only
the 50% of species with the most reliable slope estimates
were considered, however, there was a significant negative
trend between APET d coefficient and species� range limit
location, such that more southerly species were more
specific in wetter places and more northerly species were
more specific in drier places (Fig. 4f; APET d coefficient-
range limit regression: F1,19 = 4.65, P = 0.044).
D I S C U S S I O N
We found an overall trend for southerly distributed British
butterflies to be more constrained to their favoured habitats
in cooler and wetter locations. On average, there was a 44%
change in habitat specificity between the cold and warm
Proportion of population in grassland habitat
0.07 – 0.290.30 – 0.410.42 – 0.510.52 – 0.66
Figure 3 Spatial variation in niche breadth modelled for a range-
expanding butterfly species Pyronia tithonus L. (Gatekeeper).
Individuals are more constrained to their overall favoured habitat
type (grassland) in climatically unsuitable locations (black squares).
Butterfly distribution is from Fox et al. (2006) for the period 1995–
2004.
Letter Changing habitat specificity at range boundaries 1097
� 2009 Blackwell Publishing Ltd/CNRS
range limits of species within Britain (as measured by winter
temperatures, MTCO). Given that the habitat categories we
considered are very broad, we might expect even greater
differences to be apparent were finer-resolution habitat
categories to be considered. All three bioclimate variables
were important in determining spatial changes in habitat
specificity across species. Mean temperature of the coldest
month (MTCO) produced the most significant relationships,
with 71% of species (nine of which had significant slopes)
showing a pattern of more constrained habitat associations
in locations with colder winters. The moisture index APET
was also very important, and across species this bioclimate
variable most frequently best explained spatial patterns in
habitat specificity.
The final bioclimate variable, GDD5, also supported the
trend for higher habitat specificity at species� high-latitude
leading range edges. In addition, species with more southerly
distributed British ranges, and which are presumably most
constrained by climate within Britain, showed the greatest
change in their habitat associations across climate space.
For thermophilous insects such as butterflies, it is likely
that shifts in habitat associations are caused directly by
climate. This has been shown to be the case in a detailed
study of one butterfly species (Davies et al. 2006), which
suggests that climate may limit habitat use through the
existence of microclimatic thresholds (e.g. Thomas 1993;
Thomas et al. 1999; Roy & Thomas 2003; Davies et al.
2006). Our study revealed the most important bioclimate
variables affecting habitat specificity to be MTCO and the
APET moisture index. Thus, a tentative conclusion that we
might draw is that habitat associations appear to be
predominantly constrained by bioclimate variables that
relate to potential extremes; temperature of the coldest
month which may affect physiological survival, perhaps of
200 400 600 800 1000 1200
–0.0
2 –0
.04
–0.0
6 0.
00
Distribution limit (km northings)
Spe
cies
' GD
D5
β co
effic
ient
(a)
200 400 600 800 1000 1200
Distribution limit (km northings) S
peci
es' M
TC
O γ
coe
ffici
ent
–2
–4
–6
–8
–10
0
(b)
200 400 600 800 1000 1200
Distribution limit (km northings)
Spe
cies
' AP
ET
δ c
oeffi
cien
t 0
–50
–100
–1
50
50
(c)
Spe
cies
' GD
D5
β co
effic
ient
600 700 800 900 1000 1100 1200
–0.0
015
–0.0
005
0.00
05
Distribution limit (km northings)
(d)
–0.2
Spe
cies
' MT
CO
γ c
oeffi
cien
t
Distribution limit (km northings) 600 700 800 900 1000 1100 1200
–0.4
0.
0 0.
2
(e)
Spe
cies
' AP
ET
δ c
oeffi
cien
t Distribution limit (km northings) 600 700 800 900 1000 1100 1200
–4
–2
0 2
4 6
(f)
Figure 4 Effect of species� British range limit on the relationship between (a) habitat specificity and GDD5, (b) habitat specificity and MTCO
and (c) habitat specificity and APET. Panels (a–c) show all 41 species analysed, Panels (d–f) show the 21 species with the lowest standard
error of slope estimates. In panels (a and d), negative b values indicate species that show greater habitat specificity in sites with lower
accumulated annual temperatures. In panels (b and e), negative c values indicate species that show greater habitat specificity in sites with
colder winters. In panels (c and f), positive d values indicate species that show greater habitat specificity in wetter sites. The dotted line on
each panel indicates a slope coefficient of zero (no change in habitat specificity across climatic space). The bold dashed lines indicate a
significant trend from a linear regression.
1098 T. Oliver et al. Letter
� 2009 Blackwell Publishing Ltd/CNRS
the insects themselves, and drought that might predomi-
nantly act through changes in larval host plant quality.
Butterflies and their host plants may be relatively �protected�from such conditions within certain habitats. In contrast, the
total development time available (related to GDD5) appears
to have a weaker effect on spatial variation in habitat
associations, although this may allow increased abundance
through extended flight periods and more generations per
year for multivoltine species (Roy & Sparks 2000). These
conclusions are concordant with observations on the
responses of individual species to climatic extremes. Range
expansion of the sachem skipper, Atalopedes campestris
Boisduval, in southern USA has been linked to improved
over-winter survivorship with warmer winters (Crozier
2004). Also in Euphydryas editha Boisduval, aseasonal cold
caused the extinction of E. editha subpopulations associated
with one type of habitat ⁄ host plant, resulting in an
evolutionary contraction of host preference within the
metapopulation (Singer & Thomas 1996; Thomas et al.
1996). This suggests that extreme climatic conditions
commonly reduce populations to a subset of previously
occupied habitat types, followed by either gradual or limited
recovery of the original habitat range, the extent and speed
of recovery depending on whether evolutionary as well as
ecological changes have taken place. Hence, changes to the
frequency and severity of extremes associated with climate
change (in this paper represented by spatial variation in
climatic conditions) are expected to result in shifts in habitat
associations.
Changes in habitat associations could potentially also be
mediated through biotic factors (e.g. climate-related niche
shifts in host plants or natural enemies which then affect a
species� habitat associations). Biotic factors are more likely
to be important for specialist species. Many British
butterflies, however, use a number of larval host plants
and butterflies are usually attacked by generalist natural
enemies, so interactions tend to be diffuse. Indeed, seven of
the nine species that showed significant relationships
between habitat specificity and climatic variable MTCO in
our study are known as �wider countryside� rather than
�specialist� species (Asher et al. 2001), suggesting that habitat
shifts mediated solely through close interspecific interac-
tions are unlikely.
Another effect of climate on species� habitat associations
is that climate may affect population abundance and
through density dependent effects (e.g. host plant limitation,
pathogen and parasitoid aggregation) thereby alter the
relative quality of different habitat types. Thus, as popula-
tions in the favoured habitats increase, subordinate habitats
may yield increasing fitness returns relative to the main
habitats. In contrast to this density dependence hypothesis,
however, our results showed that climate was associated
with spatial patterns in habitat association independent of
butterfly abundance. The majority of species tended to be
more constrained to their favoured habitats in colder
climates even after accounting for the local abundance at
these sites. Abundance alone did not explain increasing
habitat specificity in colder places because there was no
consistent significant spatial trend across species associated
with changes in abundance.
Although we observed a significant trend among species
of more constrained habitat associations in colder places,
not all study species showed changes in habitat associations
in the direction expected. Some of these contrary results
may be simply be due to noise within the data; perhaps, for
example, because our measures of habitat type take no
account of habitat quality. Some of the variation among
species in relationships between habitat specificity and
climate, however, was explained by where species� leading
edge limits occurred in Britain. Our multispecies analysis
showed that species with more southerly British ranges were
more specific to favoured habitats in colder and wetter
places compared with species with more northern leading
edge boundaries in Britain. Furthermore, these more
southerly species tended to show steeper slopes between
habitat specificity and all three bioclimate variables (Fig. 4),
indicating that they showed the greatest change in their
habitat associations across space. This marked effect of a
local range limit suggests that the mechanisms that cause
niche shifts operate over relatively short climatic distances at
species� range edges. This would imply that niche breadth
may be relatively stable within core parts of a species� range
because abundances are at carrying capacity and ⁄ or micro-
climatic thresholds that limit habitat suitability have been
surpassed. Towards climatic range boundaries, however,
abundance may decline and ⁄ or certain habitat types become
climatically unsuitable quite abruptly; consequently there are
rapid changes in niche breadth over space close to range
boundaries.
Note that this study only investigated changes in habitat
associations at high-latitude leading boundaries of species�ranges, and we remain cautious about whether similar trends
will occur at species� trailing, low-latitude boundaries.
However, it is intriguing to observe that for species with
more reliable slope estimates (Fig. 4d–f), those with high
latitude ranges in Britain apparently show opposite trends to
southern species i.e. they appear to become more specific to
favoured habitats in warmer, drier places. Thus, we could
tentatively suggest that the bioclimate envelope of these
species may have moved sufficiently far north that they are
starting to become limited by hotter and drier, rather than
colder and wetter climatic extremes, at least in southern
England. Past evidence suggests that such dry extremes do
affect butterfly populations. In Britain, a number of
butterfly species exhibited population crashes following a
severe drought in 1976, in some cases associated with severe
Letter Changing habitat specificity at range boundaries 1099
� 2009 Blackwell Publishing Ltd/CNRS
host plant desiccation in particular habitats (Thomas 1983;
Pollard & Yates 1993). Of the species affected by this
drought, analysis of the dynamics of the ringlet butterfly,
Aphantopus hyperantus L., showed that it became constrained
to a subset of its previous habitat range (Sutcliffe et al.
1997). Likewise, exceptional droughts caused a species of
bush cricket, Metrioptera bicolour Phillipi, to disappear
disproportionately from habitat patches with uniformly
short grass in Sweden (Kindvall 1995, 1996), and for
populations of the butterfly E. editha associated with
particular habitats and host plants to become extinct in
California (Ehrlich et al. 1980).
This study holds potentially important messages for
species conservation management and for making reliable
predictions of species� future ranges. First, we have shown
that many British butterflies show significant spatial
variation in habitat associations, so a �one size fits all�national habitat management plan for each species may be
less suitable than multiple regional plans, each tailored to a
species� local needs. We suggest that conservationists should
aim to assess the habitat requirements of local populations
of their protected species and adopt relevant local habitat
management plans. Second, if habitat associations are driven
by climate, then we may expect temporal changes in habitat
association with climate change (Roy et al. 2001). Thus, we
recommend that flexibility is built into management policies,
with regular re-assessment of species� local habitat require-
ments to account for any temporal change in habitat use.
For example, a species such as the Grizzled Skipper Pyrgus
malvae L. which is currently mostly restricted to acid and
chalk grassland (6.7 and 0.2% of the UK land surface
respectively, Countryside Survey 2008) and generally in the
lowlands, could potentially expand its range by occupying
upland heath and bog sites containing one of its host plants,
Potentilla erecta L. (potentially allowing an extra 15.7% of the
UK land surface to be occupied, Countryside Survey 2008).
If niche expansion occurs as the climate warms, such that
habitat availability increases, rates of range expansion may
accelerate in future (Hill et al. 2001; Thomas et al. 2001;
Wilson et al. 2009). Conversely, contractions of habitat
availability at species� trailing, �warm� range margins might
accelerate declines over time. Models predicting range shifts
of species under future climate warming may need to
account for changes in habitat associations across spatial
and temporal climatic gradients in order to predict
probabilities of occurrence more reliably.
Currently, niche models, which are increasingly used to
inform conservation policy, often assume constancy in
habitat associations across a species� ranges (i.e. assume
spatial niche conservatism: Guisan & Zimmermann 2000;
Broennimann et al. 2007) as well as over evolutionary time
(temporal niche conservatism: Peterson et al. 1999; Marti-
nez-Meyer et al. 2004; Thuiller et al. 2005). More specifically,
the estimated coefficients which represent a species�association with different habitat types do not vary with
climate in most current formulations of generalized linear or
additive models, which are commonly used niche modelling
methods (Elith et al. 2006). We suggest that incorporating
interaction terms between habitat associations and climate
may improve the reliability of species distribution
projections.
We found that populations of species that were close to
the edge of the species� climatic range showed the most
spatial variation in habitat specificity. Therefore, to assume
constant climate–habitat associations may be most inappro-
priate when considering range boundaries. Given that many
distribution models have particular interest in the potential
expansion or contraction of species (Peterson & Vieglais
2001; Berry et al. 2002; Martinez-Meyer et al. 2004), our
results suggest that particular attention should be paid to the
constrained habitat associations evident at range boundaries.
Furthermore, recently developing models that aim to predict
niche expansion by combining demography and niche into a
single framework (e.g. Keith et al. 2008; Anderson et al.
2009) may find that population dynamics at leading
boundaries differ from dynamics towards a species� core,
due to a more limited range of climatically suitable habitat
types.
Given the current uncertainty of different species� habitat
associations over space and time, it would seem wise for
conservation policy-makers to seek to conserve the range
and ecological variability of species� habitats (Benton et al.
2003; Hopkins et al. 2007). Increasing habitat heterogeneity
may provide insurance against uncertainty both in models of
species� habitat use and also in climate change predictions.
To summarize, we present the first multispecies analysis of
climate-related spatial shifts in habitat specificity. In Britain,
we found that habitat use tends to be more constrained close
to the edges of species� climatic range boundaries, especially
in wetter regions with �cold� winter temperatures. Across the
whole globe, in any specific country the habitats used by
species will depend on the range of natural and modified
landscapes available. As bioclimatic envelopes shift with
climate warming, however, and the frequency of climatic
extremes increases, we can expect many species� niches to
change as they undergo shifts in habitat use. Understanding
climate-driven changes in species� habitat associations will
therefore be important for developing appropriate conser-
vation plans under changing climates.
A C K N O W L E D G E M E N T S
The authors are indebted to all the UKBMS volunteer
recorders for collecting data. The analysis was funded
through a NERC Ecology and Hydrology Funding Initiative
grant (NE ⁄ E011942 ⁄ 1). We thank Stephen Freeman, Nick
1100 T. Oliver et al. Letter
� 2009 Blackwell Publishing Ltd/CNRS
Isaac and Barbara Anderson for helpful discussion. Climate
data were provided by provided by Barbara Anderson and
Yvonne Collingham at York and Durham University
respectively through a UKPopNet collaboration.
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S U P P O R T I N G I N F O R M A T I O N
Additional Supporting Information may be found in the
online version of this article:
Table S1 Habitat availability–climate relationships.
Table S2 Tests for spatial autocorrelation in habitat specificity.
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Editor, David Kleijn
Manuscript received 18 June 2009
First decision made 15 July 2009
Manuscript accepted 17 July 2009
1102 T. Oliver et al. Letter
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