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ORIGINAL ARTICLE
Bayesian analysis of multi-state data with individual covariatesfor estimating genetic effects on demography
Sarah J. Converse • J. Andrew Royle •
Richard P. Urbanek
Received: 4 February 2010 / Revised: 30 March 2011 / Accepted: 1 April 2011 / Published online: 24 April 2011
� Springer-Verlag (outside the USA) 2011
Abstract Inbreeding depression is frequently a concern
of managers interested in restoring endangered species.
Decisions to reduce the potential for inbreeding depression
by balancing genotypic contributions to reintroduced pop-
ulations may exact a cost on long-term demographic per-
formance of the population if those decisions result in
reduced numbers of animals released and/or restriction of
particularly successful genotypes (i.e., heritable traits of
particular family lines). As part of an effort to restore a
migratory flock of Whooping Cranes (Grus americana) to
eastern North America using the offspring of captive
breeders, we obtained a unique dataset which includes
post-release mark–recapture data, as well as the pedigree of
each released individual. We developed a Bayesian for-
mulation of a multi-state model to analyze radio-telemetry,
band-resight, and dead recovery data on reintroduced
individuals, in order to track survival and breeding state
transitions. We used studbook-based individual covariates
to examine the comparative evidence for and degree of
effects of inbreeding, genotype, and genotype quality on
post-release survival of reintroduced individuals. We
demonstrate implementation of the Bayesian multi-state
model, which allows for the integration of imperfect
detection, multiple data types, random effects, and
individual- and time-dependent covariates. Our results
provide only weak evidence for an effect of the quality of
an individual’s genotype in captivity on post-release sur-
vival as well as for an effect of inbreeding on post-release
survival. We plan to integrate our results into a decision-
analytic modeling framework that can explicitly examine
tradeoffs between the effects of inbreeding and the effects
of genotype and demographic stochasticity on population
establishment.
Keywords Breeding � Captive productivity � Genotype
quality � Grus americana � Inbreeding coefficient �Reintroduction � Whooping crane
Introduction
Conservation biologists are frequently concerned about the
potential effects of inbreeding on the viability of popula-
tions of rare species (e.g., Frankham 1995). Crnokrak and
Roff (1999) argued that high levels of inbreeding depres-
sion could be found in wild species, including avian spe-
cies, based on differences between inbred and outbred
individuals in demographic traits such as clutch size,
hatching success, nestling survival, fledgling survival, and
adult survival. However, few direct examinations of
inbreeding depression effects on wild population demog-
raphy have been carried out, and those studies that do exist
have not integrated state-of-the-art methods in demo-
graphic estimation, such as accounting for imperfect
detection and differences in individuals based on age and
breeding state. Even so, if inbreeding effects do occur in
wild species, and the degree of the effects can be estimated,
this information can be used to inform management of
captive and restored populations.
Communicated by W. L. Kendall.
S. J. Converse (&) � J. A. Royle
Patuxent Wildlife Research Center, U.S. Geological Survey,
12100 Beech Forest Road, Laurel, MD 20708, USA
e-mail: [email protected]
R. P. Urbanek
Necedah National Wildlife Refuge, U.S. Fish and Wildlife
Service, W7996 20th Street West, Necedah, WI 54646, USA
123
J Ornithol (2012) 152 (Suppl 2):S561–S572
DOI 10.1007/s10336-011-0695-0
An example species for which concerns about inbreed-
ing have influenced management is the Whooping Crane
(Grus americana). Whooping Cranes are listed as endan-
gered under the US Endangered Species Act and Canada’s
Species at Risk Act and, as of late 2008, there were fewer
than 400 individuals in the wild, and fewer than 600 total
individuals in existence (T. Stehn, US Fish and Wildlife
Service, unpublished data). Wild Whooping Cranes exist in
3 populations, including the Aransas–Wood Buffalo Pop-
ulation (AWBP), which breeds at Wood Buffalo National
Park, Canada, and winters at Aransas National Wildlife
Refuge, USA; the Florida Non-Migratory Population in
central Florida, USA; and the Eastern Migratory Popula-
tion (EMP), which migrates between Wisconsin and Flor-
ida, USA. The last 2 are the product of reintroductions
using chicks hatched in captivity.
Whooping Cranes passed through a bottleneck during
the early twentieth century which reduced haplotype
diversity by approximately two-thirds (Glenn et al. 1999).
The AWBP, which is the source of all living Whooping
Cranes, was reduced to a low of 15 individuals in 1941.
Captive breeding of Whooping Cranes began in the 1960s,
with contributions of wild individuals (in the form of eggs
and wild-caught birds) to the captive population continuing
through the 1990s. The 2 largest captive breeding centers
are the US Geological Survey’s Patuxent Wildlife
Research Center (PWRC) in Laurel, Maryland, USA, and
the private International Crane Foundation (ICF), in Bar-
aboo, Wisconsin, USA. Several different studbooks, each
with different methods for assessing relatedness among
captive population founders, have been developed in order
to guide captive breeding decisions (Mirande 1995; Jones
et al. 2002). Studbooks are used to track the family lines of
individuals in the captive population and can be used to
produce sets of genetic statistics, including inbreeding
coefficients associated with the offspring of each potential
pairing of breeders. Captive breeding decisions have been
made with a goal of minimizing the potential for
inbreeding depression in the captive and released
populations.
There have been disproportionate contributions by
particular individuals and breeding pairs to the EMP (K.L.
Jones, University of Georgia, unpublished data) because
certain captive individuals are much more productive than
others. In order to minimize population mean kinship, and
with the ultimate goal of reducing the potential for
inbreeding depression in the EMP, two of the most pro-
ductive breeding pairs at PWRC were prevented from
producing for several years in the mid-2000s, resulting in
lower overall production. This decision could affect long-
term population viability in at least two ways. First,
because of demographic stochasticity, we expect a positive
relationship between the number of birds released and the
probability of successful establishment of the flock. This
has been demonstrated through modeling of the Florida
Non-Migratory Population (Moore et al. 2008) and
empirically for a number of different reintroduction pro-
jects (Wolf et al. 1996; Fischer and Lindenmayer 2000). In
addition, an effect of the decision to restrict the contri-
butions of the most productive pairs may be the reduction
of especially productive genotypes (i.e., heritable traits of
particular family lines) from the reintroduced population.
While there is a concern that the most successful geno-
types in a captive setting are not most successful in a wild
setting (see Frankham 2007 for a review), this is not
necessarily the case—it is possible that a positive rela-
tionship exists between the captive success and the wild
success of genotypes. If that is the case, a focus on bal-
ancing the genotypes of introduced animals, and thus
inhibiting reintroduction of the most successful captive
genotypes, may exact costs on the probability of suc-
cessfully establishing a population. However, there may be
a tradeoff if long-term viability is also compromised by
inbreeding effects.
These issues demonstrate the importance of integrating
genetic and demographic information into models that can
inform breeding and release decisions. To that end, we
wanted to provide empirical estimates that could be inte-
grated into such models, including demographic effects of
inbreeding and demographic effects of particular geno-
types, especially the most productive genotypes.
Therefore, we estimated the impacts of inbreeding on
post-release survival of Whooping Cranes in the EMP. We
also examined the impact of genotype on post-release
survival, by evaluating whether there were important dif-
ferences in individual survival as a function of parentage.
Finally, we examined whether there was a relationship
between captive productivity of dams and the post-release
survival of their offspring in order to examine whether
there is a link between the quality of a genotype in cap-
tivity and the quality of that genotype in the wild. We did
not examine a relationship between captive productivity of
sires and post-release survival of offspring (only of dams),
because the productivity of males in captivity is controlled
to a great degree by flock managers through extensive use
of artificial insemination. In the long term, it would be of
arguably greater interest to examine the impact of these
factors on post-release breeding success in addition to
survival, but because there has been little breeding in the
population during our study period, the dataset is not yet
adequate to support such an analysis.
In order to complete this work, we developed a Bayesian
multi-state model which could accommodate both live
resightings and dead recoveries (see also Barker et al.
2005; Kendall et al. 2006), multiple breeding states (i.e.,
unpaired, paired, and nester), and random effects, and
S562 J Ornithol (2012) 152 (Suppl 2):S561–S572
123
would also allow us to integrate both individual- and time-
dependent covariates into the modeling. This model has the
potential for extensive application to a wide variety of
demographic estimation problems. We provide a detailed
description of implementation of this model in WINBUGS
software (Gilks et al. 1996). Our results will support the
development of decision-analytic models (sensu Clemen
1996) which will allow for identification of optimal
breeding and release decision-making, while integrating
both genetic and demographic considerations, in order to
achieve the management objective of endangered species
conservation: long-term population viability.
Methods
Release program
Whooping Crane releases into the EMP began in 2001.
Birds were hatched at PWRC (beginning in 2001) and
ICF (beginning in 2005) in the spring of each year. Birds
hatched at PWRC were trained for ultralight aircraft-led
releases (ULR), training which consisted of early
imprinting of birds on costumed humans (such that they
will follow costumed breeding center staff and ultralight
pilots), and progressive familiarization and exercise behind
grounded ultralights operated by costumed humans. Birds
were shipped to Necedah National Wildlife Refuge
(NNWR), located in central Wisconsin, USA, in June or
July of their first year (i.e., at 1–2 months of age). Once at
NNWR, birds began training flights behind ultralights, and
were otherwise kept in pens on NNWR. Migration began
each year in October when birds were 4–5 months of age
and took up to several months, with birds flying short trips
behind the ultralights every day that weather allowed and
remaining in pens at secluded stop-over points at other
times. During the period of data collection covered by our
analysis, ultralight-led migrations terminated at Chas-
sahowitzka National Wildlife Refuge (CNWR) on Flor-
ida’s Gulf Coast. Birds remained there until they departed
of their own accord in the spring for the northward
migration. Until they departed in the spring, birds had
access to a pen and food (though they were not always
restricted to the pen). Additional details about ultra-light
led releases are provided in Urbanek et al. (2005) and
Urbanek et al. (2009).
Beginning in 2005, birds were hatched at ICF for direct
autumn release (DAR). These birds were also imprinted on
costumed humans, and shipped to a pen at NNWR, pri-
marily in early July (i.e., at \1–2 months of age). Birds
were then released directly on or near NNWR in their first
fall in the vicinity of previously released adult Whooping
Cranes, with the most desirable result being that the
released chicks would associate with the adult cranes and
follow them on their first southward migration.
Post-release, birds summered in and around NNWR,
with some birds migrating to and summering in points
farther afield, many of the latter in Michigan, USA.
Occasionally, birds that were located outside of the core
reintroduction area (on and around NNWR) during summer
were captured and relocated into the core area. In general,
released birds were able to migrate successfully on their
own after release. Northward and southward migration of
released birds occurred much more quickly than the
ultralight-led migration in the birds’ first fall, generally
over the course of a few weeks with the exception of birds
that spent at least part of the winter outside Florida (e.g.,
South Carolina, Tennessee). In Florida, birds used areas on
and near CNWR and throughout the west-central portion of
the state.
Through the 2007 year class, 114 birds were shipped
from PWRC for the ULR program and 23 birds were
shipped from ICF for the DAR program. Of these, 84
ULR program and 18 DAR program birds survived to
release and so entered our analysis. We defined release
for ULR birds as the time they began migrating north on
their own after their ultralight-led southward migration,
or, for DAR birds, the time they were released in
Wisconsin.
Birds began forming pairs in the spring of 2004, and
made the first nesting attempts in the spring of 2005.
Through the spring of 2009, of 41 nests containing eggs,
only 1, which was a renest, had successfully hatched (in
2006), and only 1 of the 2 chicks produced from that nest
successfully fledged.
Mark-resight and telemetry data
We used data collected from July 2001 through May 2008,
which included releases of 7 year classes. Birds were
affixed with colored leg bands while in pens at NNWR
prior to their first migration and with either radio or
satellite transmitters at NNWR or at the wintering site.
Attempts were made to capture released birds and replace
transmitters periodically, although this was not always
possible. The lead biologist (R.P. Urbanek) plus several
technicians monitored released birds with detections made
based on either transmitter signals, or if transmitters stop-
ped working, on colored leg bands. The focus of tracking
was on maintaining a sense of where all individuals were at
all times, which resulted in, in most cases, multiple loca-
tions weekly. However, we used monthly detections in the
multi-state model, that is, birds were either detected or not
in each month of the study period. When birds were
detected, location, activity, and social interactions were
noted. Periodically, birds were also located dead, although
J Ornithol (2012) 152 (Suppl 2):S561–S572 S563
123
not always immediately if their transmitter was not work-
ing and/or the signal was not easily located. For birds that
were found dead, the lead biologist estimated mortality
date to at least monthly precision, based on when birds
were last seen alive and on necropsy information. In just
one case, a known mortality could not be localized to a
month (rather to a multiple-month period), so we assumed
that mortality occurred during the month the bird was last
observed. Permanent removals from the population (e.g.,
because a bird was seriously injured) were also treated as
mortalities.
Living birds were classified in each time period that
they were detected as either unpaired, paired, or nester.
Whether they occupied the unpaired or paired state was
determined by the lead biologist based on observations
of social interactions between individuals; pairs were
defined as an association between 2 birds of the opposite
sex, who demonstrated territorial defense, copulation,
and/or nest building behaviors. For the nester state, birds
that laid eggs in a given year were assigned to this state
beginning in April and remained in that state through the
following March (i.e., a nester was classified as a nester
for an entire year, and no transitions were allowed into
our out of the nester state in months other than April).
Birds were assumed to change their age class each year
in June (e.g., birds occupy the first age class from release
until the following June, the second age class until the
June after that, etc.). However, we defined only 5 ages:
0, 1, 2, 3, and 4?; this age structure has been used
elsewhere for Whooping Cranes (Moore et al. 2008;
Moore et al. 2011).
Genetic information
Three different studbooks, which record individual pedi-
grees for all members of the captive population, were
compiled for Whooping Cranes using (1) historical
knowledge of the apparent relatedness of individuals that
founded the captive population, and (2) similarity coeffi-
cients based on microsatellite DNA profiles (Jones et al.
2002). Birds were collected from the AWBP to establish
the captive population between 1967 and 1998. Originally,
individuals collected from different composite nesting
areas (CNAs; distinct nesting territories at Wood Buffalo
National Park, Canada, to which nesting pairs return
annually) were assumed to be unrelated (Mirande 1995).
Information derived from leg banding data, based on bands
put on juveniles at AWBP from 1977 to 1988 (Canadian
Wildlife Service and U.S. Fish and Wildlife Service 2005)
was used to develop a studbook (the LG studbook; Jones
et al. 2002) which integrated information on known rela-
tionships between birds in different CNAs. For example, a
pair from one CNA might have hatched a chick that was
banded, and that chick was then known to have become a
member of a breeding pair at another CNA. If both these
pairs contributed a founder, these founders would be
known to be related.
However, because of the severe bottleneck that
Whooping Cranes passed through, an assumption of unre-
latedness in founder birds that were not known to be related
based on banding data is not valid, and estimates of
inbreeding calculated from the LG studbook will be min-
imum measures of inbreeding. Therefore, 11 microsatellite
loci were assessed to more thoroughly determine related-
ness among founders (Jones et al. 2002). Two different
methods were used to assess relatedness, producing 2 dif-
ferent microsatellite-generated studbooks, including the
number of allelic positions shared between 2 individuals
divided by the total number of positions assessed (pro-
ducing the AS studbook; Blouin et al. 1996) and the more
complex method producing the QG studbook (Queller and
Goodnight 1989), which measures relatedness based on
whether individuals share alleles at a higher or lower than
average rate. As expected, integration of microsatellite
information into the studbooks substantially increased the
assessed relatedness of birds in the captive breeding pop-
ulation (Jones et al. 2002).
Various statistics are calculable based on the studbooks,
including the coefficient of inbreeding, an index of the
relatedness of an individual’s parents. Despite the avail-
ability of studbooks integrating microsatellite data, captive
breeding of Whooping Cranes has been and is still largely
managed to minimize the inbreeding coefficient arising
from the LG studbook, 0 B I - LG B 1. The result is that
there is essentially no variation in inbreeding coefficient in
the reintroduced population based on the LG studbook
measures (all offspring have inbreeding values &0).
Therefore, we focused our attention on the measures of
inbreeding from the microsatellite studbooks, which give a
different picture of inbreeding in the captive and released
populations, and which vary substantially across released
individuals. An individual’s inbreeding coefficient based
on both the AS studbook, 0 B I - AS B 1, and the QG
studbook, -1 B I - QG B 1 increase with greater relat-
edness of the parents.
Multistate modeling
We model the state of individual i at time t, Zi,t, conditional
on the state at the previous time period (i.e., state transi-
tions are first-order Markovian) and we assume that the
state-transition probabilities depend on previous state, as
well as factors that are individual- and time-specific.
Because the state-space is discrete, we denote the state
model by the following short-hand notation for describing
a categorical random variable:
S564 J Ornithol (2012) 152 (Suppl 2):S561–S572
123
Zi;tjZi;t�1�Cat Ti;t;Zi;t�1
� �ð1Þ
where i specifies the individual and t specifies the time
period (i.e., month) and Ti;t;Zi;t�1is the vector of state-
transition probabilities for individual i, at time t - 1, given
that individual i was in state Zi;t�1 at time t - 1. Equiva-
lently, the state an individual occupies in month t, depen-
dent on the state in the previous month, is a multinomial
trial with multinomial cell probabilities Ti;t;Zi;t�1:
The observation of individuals is described by variable
Xi,t which is 1 if individual i is observed at time t and 0
otherwise. We specify a model for Xi,t such that,
Xi;tjZi;t�BernðpZi;tÞ ð2Þ
where detections arise from a Bernoulli distribution with
detection probability, p, which depends only on the state an
animal occupies when detected (though we note that
detection probability could easily be made to depend on
individual and time as well; see further comments on this
issue below).
We defined states 1:5 in the model: unpaired (1),
paired (2), nester (3), newly dead (4), and unobservable
dead (5). Birds only occupied the newly dead state in the
month that they died, and were observable in that state. In
the following month, they transitioned deterministically
into the unobservable dead state. Use of a newly dead
state to model mortality in a multi-state context was
previously described by Lebreton et al. (1999). The state
transition probabilities Ti;t;Zi;t�1
� �were then specified as a
function of conditional state transitions (c) and survival
(u) as follows:
ð3Þ
The last two rows in this matrix ensure that a bird can
occupy the newly dead state in only one time period, we
can then use the observation model to ensure that birds
are only recoverable in the first month they die (in
practice, birds are recovered after their first month dead,
but the month of death is determined as described
above). Note that the left-most 0 in the top row
restricts movement directly from the unpaired to the
nester state.
Generally, we can use a multinomial logit function to
model the c parameters to ensure that the state transition
probabilities sum to 1. This can be achieved by speci-
fying, for example, for transitions out of the paired
state:
c 2;1ð Þ;i;t ¼p 2;1ð Þ;i;t
1þ p 2;1ð Þ;i;t þ p 2;3ð Þ;i;tð4aÞ
and
c 2;3ð Þ;i;t ¼p 2;3ð Þ;i;t
1þ p 2;1ð Þ;i;t þ p 2;3ð Þ;i;tð4bÞ
and
c 2;2ð Þ;i;t ¼ 1� c 2;1ð Þ;i;t � c 2;3ð Þ;i;t ð4cÞ
such that we calculate the probability of remaining in a
state by subtraction. We then specify models for the pusing a log function, such as:
logðp 2;1ð Þ;i;tÞ ¼ b 2;1ð Þ: ð5Þ
More simply, if only 2 transitions from a particular state
are possible, one of these can be modeled directly as a logit
function. For example (for transitions out of the unpaired
state):
logit c 1;2ð Þ;i;t
� �¼ b 1;2ð Þ ð6aÞ
and
c 1;1ð Þ;i;t ¼ 1� c 1;2ð Þ;i;t ð6bÞ
Specifically for Whooping Cranes in the EMP, we
modeled state transition probabilities as a function of the
state, sex, and, for unpaired birds, the age of the individual,
where age was 0, 1, 2, 3, or 4? years. We also included a
random effect of month. This effect applied over
83 months for the transitions between the unpaired and
paired states, but for transitions into and out of the nester
state, because these were only allowed to occur in April,
the random effect applied over just 7 months, i.e., in 7
Aprils. Transitions into and out of the nester state were not
allowed in all other months. We specified:
logit c 1;2ð Þ;i;t
� �¼ b 1;2ð Þ;sexi
þ b 1;2ð Þ;agei;tþ b 1;2ð Þ;t; ð7aÞ
where b 1;2ð Þ;t�Norm bð1;2Þ; rð1;2Þ� �
; and for (q,r) = (2,1),
(2,3), (3,1), and (3,2):
log p q;rð Þ;i;t� �
¼ b q;rð Þ;sexiþ b q;rð Þ;t ð7bÞ
where the b q;rð Þ;t are intercepts for each of the state tran-
sitions, r(q,r) are transition-specific standard deviations of
the monthly random effect normal hyper-distributions, the
b q;rð Þ;sexiare fixed effects of sex for each of the state tran-
sitions, and the b 1;2ð Þ;agei;tare age-specific effects of each of
the 5 age classes on transition from the unpaired to the
paired state.
Note that, although, as described below, we included a
release type effect (ULR vs. DAR) in the models of sur-
vival, we did not consider this effect for state transitions.
J Ornithol (2012) 152 (Suppl 2):S561–S572 S565
123
This was because no DAR birds had left the unpaired state
during the period our analysis covers, as the DAR program
was not initiated until 2005 and the DAR birds were on
average much younger than the ULR birds. Also, for the
transitions out of the paired and nester states, we did not
estimate age effects because most of the birds in those
states were in only the 3 and 4? age classes.
For survival, we built basic logit models with survival as
a function of state, age, sex, and release type, and again, we
also included a random effect of month. The model for
unpaired survival, u 1ð Þ;i;t; was:
log it u 1ð Þ;i;t
� �¼ a 1ð Þ;agei;t
þ a 1ð Þ;sexiþ a 1ð Þ;releasetypei
þ a 1ð Þ;t;
ð8aÞ
where a qð Þ;t�Norm aðqÞ; rðqÞ� �
and for paired (q = 2) and
nester (q = 3) survival:
log itðu qð Þ;i;tÞ ¼ a qð Þ;sexiþ a qð Þ;t: ð8bÞ
Again, we did not include release type effects in the
paired and nester state models because only ULR birds
occupied those classes during the period our analysis
covers, and we did not consider age effects because birds in
those states were primarily in the older age classes.
The survival models (for all states) also had one other
parameter associated with a genetic variable. We used
6 different genetic variables, including measures of
inbreeding from the AS studbook, I-AS, and the QG
studbook, I-QG (from Jones et al. 2002) as well as dam,
sire, breeding pair, and dam productivity (a surrogate for
genotype quality). We standardized each of the inbreeding
values to have mean 0 and standard deviation 1. For the
dam effect, we identified 24 different dams that had
contributed chicks to our dataset, then we fit the 24 dam-
specific effects adamið Þ as random effects, where dam-
specific effects were assumed Normð0; rdamÞ: For sire, there
were 23 males that had contributed chicks to our dataset,
and the asireiwere assumed Normð0; rsireÞ: There were 30
unique combinations of dam and sire (i.e., breeding pair)
represented in our dataset; while breeding individuals have
only a single social mate (with whom they are housed)
extensive use of artificial insemination results in a greater
number of pairs than breeding individuals of either sex.
These breeding pair effects, apairi; were modeled as
Normð0; rpairÞ: Finally, we also examined the relationship
between a dam’s genotype quality, as measured by her
productivity as a captive breeder, and the survival of her
offspring. We used the number of chicks that a dam had
contributed to EMP releases (defined as chicks shipped to
Wisconsin from the breeding centers); we also standard-
ized this variable as described above. Note that the coef-
ficients for the genetic variables were not superscripted
with q; we did not estimate separate effects for the different
states. We then ran 6 separate models, one with each of the
different genetic effects, and, for inference, examined the
posterior distributions of the genetic effects: Inbreeding-
AS, with parameter aI�ASi; Inbreeding-QG, with parameter
aI�QGi; Dam, with parameter rdam, Sire, with parameter
rsire, Pair, with parameter rpair, and Dam Productivity, with
parameter aprodi: We based our inference on these genetic
effect parameter estimates, their magnitude, direction, and
95% credible intervals. Conceivably model selection could
be used to rank these 5 models, but we did not carry out
formal model selection because we were primarily inter-
ested not in which model was best but in the effect esti-
mates and their uncertainty, which we plan ultimately to
integrate into decision-support models for informing
breeding and release decisions in this population (see
‘‘Discussion’’). Moreover, we note the substantial diffi-
culties associated with model selection, as described by
Link and Barker (2006) and Millar (2009), which will only
be increased by the inclusion of random effects.
Finally, detection probabilities varied only by state, and
were modeled on the logit scale, resulting in 4 parameters:
s(1), s(2), s(3), and s(4). For state 4, the detection probability
is, more precisely, the probability of dead recovery in the
month an animal dies. We did originally attempt to build
models with additional structure on p (in particular, time
and individual random effects), but found that these models
were very slow to converge, which indicated to us that our
data could not support this additional structure.
We specified uniform prior distributions, Unif(-10,10)
for all parameters except for r(q), …, r(q,r), rdam, rsire, and
rpair, which had prior distributions Unif(0,10). Analyses of
the 6 different models (Inbreeding-AS, Inbreeding-QG,
Dam, Sire, Pair, and Dam Productivity) were conducted
using the computational software WinBUGS (Gilks et al.
1996). For each of 3 independent Markov chains, we ran
7,000 samples (14,000 samples for the Dam, Sire, and Pair
models, which, containing an additional random effect,
required additional samples to obtain good convergence)
after discarding an initial 2,000 samples (4,000 samples for
the Dam, Sire, and Pair models), for a total of 15,000
samples (30,000 samples for the Dam, Sire, and Pair
models) from which we made inference. These sampling
parameters were adequate to obtain good model conver-
gence, based on visual inspection of the chains and on R_
generally \1.2 as recommended by Gelman et al. (2004).
Individuals for which data were missing were dropped
from the analysis; these included 2 wild-hatched individ-
uals and 3 other individuals for whom inbreeding coeffi-
cients were not available.
To implement the model in WinBUGS, data input
included 2 matrices, each of dimension ‘number of
S566 J Ornithol (2012) 152 (Suppl 2):S561–S572
123
individuals’ by ‘number of months’. One was a matrix of
detections (X), this matrix was equal to ‘NA’ (i.e., missing
or irrelevant data) before a bird entered the dataset (i.e.,
before it was released), ‘1’ when a bird was detected, and
‘0’ when a bird was not detected. If a bird was known to
have died (i.e., was recovered dead), X was ‘1’ in the
month of mortality, and ‘0’ thereafter. The second matrix
was a state matrix (Z), which was equal to ‘1’, ‘2’, ‘3’, or
‘4’ if a bird was detected in the unpaired, paired, nester, or
dead states, respectively, in a given month, and ‘NA’
otherwise. If a bird was observed in the dead state in
1 month (i.e., was recovered dead and death occurred in the
given month), then in subsequent months the individual’s
state became ‘5’—birds in this state were dead but unob-
servable. We also specified 2 vectors of length ‘individu-
als’: vector F recorded the month of release and vector
L specified either the month an individual was known to
have died or, for individuals not recovered dead, the end of
the study period; these vectors bounded the likelihood for
each individual. Additional input data included the number
of individuals (i) and months (t) in the dataset, as well as
the various individual- and time-dependent covariates used
in modeling. An R (R Development Core Team 2004)
script, using the library R2WinBUGS (Sturtz et al. 2005),
and input data files necessary to run the ‘‘Dam’’ model can
be obtained from the first author.
Results
Our analysis included data on 102 released individuals.
Thirty-five of those birds were known to have entered the
paired state at some point during the study period, and 26 of
those were further known to have entered the nester state.
Sixty-eight birds were known to have died during the study
period. ULR birds were included in the analysis from 7
release cohorts (2001 n = 5; 2002 n = 16; 2003 n = 16;
2004 n = 13; 2005 n = 19; 2006 n = 1; and 2007 n = 14).
DAR birds were included from 3 cohorts (2005 n = 4; 2006
n = 4; and 2007 n = 10). The low number in the 2006 ULR
cohort was due to a mortality event which occurred at the
wintering site in Florida, where all but one of the year’s
chicks was killed by an apparent lightning strike to a pen;
one individual escaped and was free roaming in Florida
until its death a few months later (Fig. 1).
Of greatest interest are the estimates of the genetic
effects on survival. Based on the IAS measure, the effect of
inbreeding was 0.02 (95% CI = -0.36, 0.39; Table 1);
54% of the mass of this posterior distribution was \0.
Based on the IQG measure, the estimate was -0.15 (95%
CI = -0.51, 0.22; Table 1); 78% of the mass of this
posterior distribution was \0. This suggests that there is
virtually no effect of inbreeding based on the IAS measure
but that there is some indication of a negative effect of
inbreeding on survival based on the IQG measure. We
present predicted annual survival probabilities, based on
the Inbreeding-QG model, for unpaired birds with
inbreeding coefficients across the range of values for birds
in our dataset (Fig. 2). Annual survival probabilities of the
offspring of the various dams, sires, and pairs are shown in
Figs. 3, 4, and 5, respectively; these figures suggest much
greater sampling uncertainty within individuals (or pairs)
versus variation between individuals (or pairs) which is not
surprising given the sample size of chicks from each
individual or pair. Finally, the effect of dam productivity
on post-release success was 0.20 (95% CI = -0.18, 0.60;
Table 1); 84% of the mass of the posterior distribution was
greater than 0. Predicted annual survival probabilities for
the offspring of dams with productivity (i.e., number of
offspring contributed to the EMP) across the range of birds
in our dataset are provided (Fig. 6).
Basic demographic patterns in this reintroduced popu-
lation are also of interest. Birds appeared to have sub-
stantially higher survival in the paired and nester states,
which suggests a benefit of pairing, though these birds are
also older, on average, than unpaired birds (Table 2; all
estimates are based on the Inbreeding-AS model but these
estimates varied little across the 5 different models).
Annual state transition probabilities also showed inter-
esting patterns. First, from the paired state, birds were
much more likely to become nesters than to become
unpaired (Table 2). This suggests that pairing is a good
indicator of future nesting. Second, transitions out of the
nester state were near 0 (Table 2), such that birds that
nested once were likely to continue to nest in subsequent
years.
We note that estimated transitions from the unpaired
into the paired state were lowest, as expected, in the 0-year-
old age class, but also were highest in the 3-year-old age
class (b 1;2ð Þ;age¼0 : b 1;2ð Þ;age¼4þ; Table 1). An indication of a
Fig. 1 States and state transitions used to model demographics of
Whooping Cranes (Grus americana) in the Eastern Migratory
Population, reintroduced to the eastern United States
J Ornithol (2012) 152 (Suppl 2):S561–S572 S567
123
higher pairing probability in 3-year-old versus 4?-year-old
birds is consistent with patterns observed in the Florida
Non-Migratory Population (Moore et al. 2008).
Finally, we also note an indication of lower survival
in the DAR cranes as compared to the ULR cranes
(a 1ð Þ;releasetype; Table 1) in the unpaired state. When con-
verting monthly to annual survival (based on estimates
from the Inbreeding-AS model), the survival estimate was
0.90 (95% CI = 0.83, 0.96) for unpaired ULR birds and
0.84 (95% CI = 0.65, 0.97) for unpaired DAR birds.
Discussion
A seminal paper by Lande (1988) suggested that the
importance of demographic factors would generally out-
strip the importance of genetic factors in determining the
fate of endangered species. This argument caused extensive
controversy within the conservation genetics community
(see Frankham et al. 2002 for a review). However, Lande
went on to emphasize the importance of understanding
the ‘‘interaction of demographic and genetic factors in
Table 1 Selected parameter estimatesa (mean, 95% credible interval) related to survival and breeding state transitions of Whooping Cranes
(Grus americana) in the Eastern Migratory Population
Survival Model Parameters Mean (95% CI) Transition Model Parameters Mean (95% CI)
a 1ð Þ;age¼0b -1.00 (-2.17, -0.04) b 1;2ð Þ;age¼0
l -5.82 (-9.77, -1.71)
a 1ð Þ;age¼1 0.21 (-0.73, 1.04) b 1;2ð Þ;age¼1 1.05 (-0.22, 2.40)
a 1ð Þ;age¼2 -0.33 (-1.23, 0.49) b 1;2ð Þ;age¼2 2.08 (0.80, 3.39)
a 1ð Þ;age¼3 1.56 (-0.09, 4.51) b 1;2ð Þ;age¼3 2.48 (1.13, 3.89)
a 1ð Þ;age¼4þ -0.44 (-1.54, 0.70) b 1;2ð Þ;age¼4þ 0.21 (-2.36, 2.13)
a 1ð Þ;sexc -0.12 (-0.53, 0.27) b 1;2ð Þ;sex
m -0.20 (-0.56, 0.17)
a 2ð Þ;sex 1.26 (-0.93, 3.68) b 2;1ð Þ;sex 0.14 (-0.59, 0.89)
a 3ð Þ;sex -0.03 (-1.65, 1.62) b 2;3ð Þ;sex 0.01 (-0.64, 0.65)
a 1ð Þ;releasetyped 0.23 (-0.37, 0.78) b 3;1ð Þ;sex 3.83 (-0.45, 9.10)
r 1ð Þ;month (all months)e 0.62 (0.08, 1.38) b 3;2ð Þ;sex 0.15 (-6.37, 6.78)
r 2ð Þ;month (all months) 1.23 (0.09, 3.15) r 1;2ð Þ;month (all months)n 2.78 (1.60, 4.36)
r 3ð Þ;month (all months) 2.91 (0.88, 5.25) r 2;1ð Þ;month (all months) 2.67 (0.52, 5.58)
aI�ASf 0.02 (-0.36, 0.39) r 2;3ð Þ;month (April only) 2.38 (0.53, 7.55)
aI�QGg -0.15 (-0.51, 0.22) r 3;1ð Þ;month (April only) 4.41 (0.19, 9.74)
rdamh 0.54 (0.07, 1.39) r 3;2ð Þ;month (April only) 3.82 (0.12, 9.55)
rsirei 0.38 (0.01, 1.11)
rpairj 0.49 (0.05, 1.27)
aprodk 0.20 (-0.18, 0.60)
a With exception of the genetic effects, all estimated effects are from the Inbreeding-AS modelb Differential effects, from the mean, of each age class on unpaired survivalc Differential effects, from the mean, of being a male on unpaired (q = 1), paired (q = 2), and nester (q = 3) survivald Differential effect, from the mean, of being a direct autumn release bird on unpaired survivale Standard deviation of the random effect of time on unpaired (q = 1), paired (q = 2), and nester (q = 3) survivalf Blouin et al. (1996) inbreeding effect on survival, from Inbreeding-AS modelg Queller and Goodnight (1989) inbreeding effect on survival, from Inbreeding-QG modelh Standard deviation of the random effect of dam on survival, from Dam modeli Standard deviation of the random effect of sire on survival, from Sire modelj Standard deviation of the random effect of pair on survival, from Pair modelk The effect of dam productivity (number of a dam’s offspring) on survival, from Dam Productivity modell Differential effects, from the mean, of each age class on transitions from the unpaired to paired statem Differential effects, from the mean, of being a male on transitions from unpaired to paired (q = 1,2), paired to unpaired (q,r = 2,1), paired to
nester (q,r = 2,3), nester to unpaired (q,r = 3,1), and nester to paired (q,r = 3,2) statesn Standard deviation of the random effect of time on transitions from unpaired to paired (q = 1,2), paired to unpaired (q,r = 2,1), paired to
nester (q,r = 2,3), nester to unpaired (q,r = 3,1), and nester to paired (q,r = 3,2) states
S568 J Ornithol (2012) 152 (Suppl 2):S561–S572
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extinction.’’ We propose decision-analytic modeling (sensu
Clemen 1996) as a practical approach to examining this
interaction and making optimal decisions in the face of
both demographic and genetic considerations. By devel-
oping models that will project the impacts of various
breeding and release decisions through time on the ultimate
goals of endangered species recovery, generally framed as
long-term population viability, we can examine the weight
of evidence in favor of various decision rules (e.g., mini-
mize population mean kinship in releases, maximize the
number of individuals released, etc.). Such models must
Fig. 2 Predicted annual survival, with 95% credible intervals, of
unpaired released Whooping Cranes (Grus americana) as a function
of the individual’s inbreeding coefficient, based on Queller and
Goodnight’s (1989) measure of relatedness applied to microsatellite
analysis (Jones et al. 2002). Higher coefficients indicate greater
relatedness
Fig. 3 Predicted annual survival, with 95% credible intervals, of
unpaired released Whooping Cranes (Grus americana) as a function
of the individual’s dam. Dams are arranged in descending order of the
number of chicks they contributed to our dataset. Dams 1 and 2 were
removed from production in 2006 to maintain genotypic balance in
the Eastern Migratory Population
Fig. 4 Predicted annual survival, with 95% credible intervals, of
unpaired released Whooping Cranes (Grus americana) as a function
of the individual’s sire. Sires are arranged in descending order of the
number of chicks they contributed to our dataset. Sires 1 and 2 were
removed from production in 2006 to maintain genotypic balance in
the Eastern Migratory Population
Fig. 5 Predicted annual survival, with 95% credible intervals, of
unpaired released Whooping Cranes (Grus americana) as a function
of the captive breeding pair that produced the individual. Pairs are
arranged in descending order of the number of chicks they contributed
to our dataset. Pairs 1 and 2 were removed from production in 2006 to
maintain genotypic balance in the Eastern Migratory Population
J Ornithol (2012) 152 (Suppl 2):S561–S572 S569
123
integrate both the effects of inbreeding and the effects of
individual quality on the future demographic performance
of Whooping Crane populations.
Our first step in developing decision-analytic models has
been estimation of the effects of factors such as inbreeding,
genotype, and genotype quality on demographic perfor-
mance. The next steps will involve developing basic indi-
vidual-based population projection models, and then
integrating the effects of inbreeding into those models. The
effect estimates we have reported here include substantial
uncertainty, and this uncertainty will be integrated directly
into the decision-analytic models, such that the projection
of the effect of inbreeding, for example, will be simulated
in the decision-analytic models from the posterior distri-
bution of the inbreeding effect parameter. As a first pro-
totype, we will then be able to examine tradeoffs between
demographic stochasticity and inbreeding in decisions
about whether to release more Whooping Cranes with
higher population mean kinship, or fewer cranes with lower
population mean kinship, by projecting inbreeding coeffi-
cients of birds in the population through time (e.g., by
assuming random mating). Future refinements will inte-
grate the impacts of genotype quality on these decisions.
Our results suggested a negative effect of inbreeding on
survival of offspring, at least based on the IQG measure.
Though the uncertainty around the effect estimate was
substantial, we note that 78% of the mass of the posterior
distribution for this effect estimate was \0. Analysis of
individual dam, sire, and pair effects did not indicate that
the particular dams, sires, or pairs that had been removed
from production had produced offspring with clearly higher
survival rates, due to the large sampling variance, though
we note that the survival point estimate for the offspring of
the most productive dam, most productive sire, and most
productive pair (right-most points in Figs. 3, 4, and 5,
respectively) were the second highest for any dam, sire, or
pair. There was also some indication that breeding females
that were more successful in captivity (based on produc-
tivity) had offspring that were more successful post-release
(based on survival). Though again, there was substantial
uncertainty around the effect estimate, 84% of the mass of
the posterior distribution was [0. We note that the corre-
lation between the number of chicks from a given dam
shipped to Wisconsin and the number of chicks from that
Fig. 6 Predicted annual survival, with 95% credible intervals, of
unpaired released Whooping Cranes (Grus americana) as a function
of the number of offspring of an individual’s dam that were released
to the Eastern Migratory Population
Table 2 Average annual survival probabilities and average monthly state transition probabilities for Whooping Cranes (Grus americana) in the
Eastern Migratory Populationa
State Annual survival probabilityb (95% CI) State transition Annual transition probabilityc (95% CI)
Unpaired 0.877 (0.791, 0.963) Unpaired to unpaired 0.993 (0.970, 0.999)
Unpaired to paired 0.007 (0.001, 0.030)
Paired 0.991 (0.940, 0.999) Paired to unpaired 0.044 (0.001, 0.179)
Paired to paired 0.459 (0.000, 0.916)
Paired to nester 0.498 (0.041, 0.958)
Nester 0.991 (0.939, 0.999) Nester to unpaired 0.030 (0.000, 0.347)
Nester to paired 0.016 (0.000, 0.143)
Nester to nester 0.955 (0.448, 1.000)
a All estimates in table are based on the Inbreeding-AS model; mean estimates varied little from model to modelb Survival was estimated on a monthly time step and then annualized (uannual = umonthly
12 )c Transition probabilities were calculated on a monthly time step, except for transitions into and out of the nester state, which were only allowed
to occur in April, and so in effect were estimated naturally on an annual scale. Transitions between the unpaired and paired states were
annualized as: cannual = 12 9 cmonthly 9 (1 - cmonthly)11, i.e., as the probability of making a transition exactly once during the year. The
probabilities of remaining in a given state were calculated by subtraction from the relevant annual probabilities, as described in the text
S570 J Ornithol (2012) 152 (Suppl 2):S561–S572
123
dam that were actually released was 0.97, suggesting that
our finding was not due to having all but the phenotypically
strongest of a dam’s chicks die prior to release.
There are future improvements to be made in this
analysis. Most notably is that, with additional data, it will
be feasible to examine impacts of inbreeding, genotype,
and genotype quality on reproductive behavior (e.g., pair-
ing and nesting probabilities). Through May of 2008, there
were relatively few breeders in the population, but with
continued data collection, closer analysis of breeding state
transitions may reveal important patterns. First, it may be
that breeding behavior is a more important indicator of
population success than survival, as survival in the EMP
has been fairly good to date (based on comparisons with
survival in the AWBP; Link et al. 2003) while breeding has
not been very successful (only 1 individual fledged from 24
nests through May of 2008); thus reproduction appears to
be the limiting factor in establishment of the EMP. In
addition, given that our measure of genotype quality was
dam productivity, there is a stronger argument for an
expectation of correlation between a dam’s productivity in
captivity and her offspring’s productivity in the wild (an
analysis that will be possible in the near future), rather than
with her offspring’s survival in the wild. Related to this
point, we are interested in developing better measures of
genotype success from captive birds, especially for male
birds, though this will be challenging. Given how closely
birds’ breeding contributions are managed in captivity, a
genotype has limited ability to express its quality, though
we note that, given the health care that birds receive, this
point would be likely even more true if we had used captive
survival as a metric of individual quality for captive birds.
Finally, a stronger genetic description of the captive flock
will be beneficial in examining the effects of inbreeding.
This may be accomplished in the future either by analysis
of additional microsatellites, or, more promising still,
mapping of the Whooping Crane genome (K.L. Jones,
University of Georgia, personal communication).
On a more technical level, further development is needed
on goodness-of-fit procedures for Bayesian multi-state
models. Currently, technology does not exist for assessing fit
of these models. While, with binary data, investigators have
used posterior predictive assessment to evaluate fit (e.g.,
Green et al. 2009), the appropriate fit statistics have not been
developed for data of the type we analyze here. However, we
note that, while we did not conduct goodness-of-fit, a lack of
fit would only serve to increase the already large 95%
credible intervals around the genetic effect coefficients, and
would not substantially change our inference.
While the success of the EMP is in doubt, largely
because of mass nest failures, apparently due to nest
abandonment, the survival and state transition probabilities
that we estimated provide some hope. First, we note that
survival has been higher in the EMP than in the Florida
Non-Migratory Population and on a par with birds in the
AWBP (Link et al. 2003; Moore et al. 2008; Moore et al.
2011). Second, while transitions from the unpaired into the
paired state were low, this was likely due to the young
age of the birds; in May 2008, 24% of the birds were in age
class 0, 5% in age class 1, 23% in age class 2, 13% in age
class 3, and 36% in age class 4?. And third, state transi-
tions from the paired and nester states were heartening—
once birds became paired, they were more likely to nest
than they were to become unpaired, and once birds nested,
they were unlikely to stop nesting in subsequent years.
Finally, we did find evidence that release type had an effect
on post-release survival, but if DAR birds prove to be more
successful breeders than their ULR counterparts (because
releases of DAR birds began only in 2005, these individ-
uals were as yet too young to have entered breeding states
by the end of our study period), there will be a strong
argument in favor of continuing this release method.
Acknowledgments We thank Ken Jones who provided the
inbreeding coefficients. We thank the field and breeding center staff
who were involved in collecting and providing data, especially J.
Chandler, A. Fasoli, B. Hartup, M. Wellington, and S. Zimorski. We
extend our appreciation to the Whooping Crane Eastern Partnership
for facilitating our collaboration and to the National Fish and Wildlife
Foundation for funding this work. D. Diefenbach, K. Jones, E. Zipkin,
and one anonymous reviewer provided helpful reviews of the draft
manuscript. Use of trade, product, or firm names does not imply
endorsement by the U.S. Government.
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