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* CNRS UMR 5554–Institut des Sciences de l'Evolution, Université Montpellier 2, 34095 Montpellier, Cedex 5, France, Laboratoire Population-Environnement-Développement, UMR D151, Université de Provence-IRD, 13331 Marseille, Cedex 3, France and School of Biological Sciences, University of Reading, Whiteknights, Reading RG6 6BX, United Kingdom
1 Corresponding author: CNRS UMR 5554–Institut des Sciences de l'Evolution Université Montpellier 2–CC64, Place E. Bataillon 34095, Montpellier, Cedex 5, France.
E-mail: bnabholz{at}univ-montp2.fr
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ABSTRACT |
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 TOP ABSTRACT MATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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Several reports, however, have recently questioned the relevance of mtDNA as a marker of population size and history (BALLARD and WHITLOCK 2004; HURST and JIGGINS 2005; BAZIN et al. 2006). Among these, the BAZIN et al. (2006) study proposed that patterns of mtDNA diversity in animals are largely influenced by adaptive evolution. First, BAZIN et al. (2006) showed that the average level of within-species mtDNA diversity is not correlated to factors presumably influencing the effective population size: invertebrate species, for example, are not more polymorphic than vertebrates, marine mollusks are not more polymorphic than continental ones, and small, planktonic crustaceans are not more polymorphic than large, benthic ones. Nuclear loci, in contrast, behave essentially as expected under the nearly neutral model. Second, BAZIN et al. (2006) reported a higher fixation rate of amino-acid substitutions in species with a large population size, while the opposite would be expected under the nearly neutral theory. These results were interpreted as reflecting the recurrent fixation of adaptive changes in mtDNA, consistent with GILLESPIE's (2000, 2001) genetic draft theory. It was proposed that selective sweeps associated to the fixation of favorable mutations (MAYNARD SMITH and HAIGH 1974) lead to frequent drops of mtDNA variability, removing any detectable influence of effective population size on the mitochondrial diversity (BAZIN et al. 2006).
By questioning the near-neutrality assumption, this and other studies cast doubts on the reliability of mtDNA as a marker of species demography: under the genetic draft model, the mitochondrial diversity of a given species is primarily determined by the time since the last selective sweep, irrespective of population size. If confirmed, this result may have important practical consequences and would call for a reappraisal of many population genetic studies based on mtDNA. Further assessment of this strong claim therefore appears worthwhile.
Several limitations of the BAZIN et al. (2006) study stress the need for additional investigations. First, this study was done at a relatively high taxonomic level and therefore involved comparing the genetic diversity of highly divergent species (e.g., mammals and mollusks). Life-history traits are obviously not comparable between organisms that differ, so the link between the genetic diversity and the biology of species, if any, is difficult to make. The basic properties of the mitochondrial genome, furthermore, might vary between distantly related taxa. The BAZIN et al. (2006) approach, for example, did not properly account for potential variations in mitochondrial and nuclear mutation rates across animal phyla (MARTIN and PALUMBI 1993; LYNCH et al. 2006), although several of their results are robust to this nuisance parameter.
Second, and most importantly, it is unclear from BAZIN et al. (2006) whether adaptive mitochondrial evolution is effective in all animal phyla. Gillespie's model predicts a merely flat relationship between genetic diversity and effective population size (Figure 1): small populations undergo genetic drift, and large populations undergo genetic draft. The population adaptive mutation rate is obviously higher in large populations, which compensates for the decrease in genetic drift. The results of BAZIN et al. (2006) strongly suggest that the mtDNA diversity of invertebrate species is reduced by the recurrent fixation of advantageous mutations: invertebrates probably belong to the "draft zone" (Figure 1). But the location of vertebrate species in Gillespie's scheme is unclear. Although they do not exclude mitochondrial adaptation in vertebrates as well, the results of BAZIN et al. (2006) do not appear incompatible with an evolutionary process dominated by genetic drift in this group. This is an important issue because a large fraction of the mtDNA-based population and conservation genetics literature focuses on vertebrates. The question has been preliminarily addressed by MULLIGAN et al. (2006). Reanalyzing the Bazin et al. data, these authors reported a positive correlation between the average mtDNA nucleotide diversity and allozyme heterozygosity of eight mammalian orders, suggesting that mammalian mtDNA could belong to the "drift zone" (see Figure 1).
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Our primary goal was to reproduce the BAZIN et al. (2006) approach to check whether evidence for mitochondrial adaptive evolution is detected at this lower taxonomic level. Does mtDNA diversity correlate to nuclear diversity at this scale? Is there an excess of fixation of nonsynonymous changes? Then we planned to investigate whether the mtDNA diversity of mammalian species can be predicted from life-history and ecological variables, as would be expected if the effective population size was a strong determinant of the mtDNA diversity. Are small mammals more polymorphic, on average, than large ones? Are carnivorous predator species less diverse than herbivorous prey? The relationship between life-history traits and genetic diversity in mammals was explored decades ago using allozymes (RYMAN et al. 1980; WOOTEN and SMITH 1985; SAGE and WOLFF 1986) and yielded equivocal results. A reanalysis using sequence data would appear timely.
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MATERIALS AND METHODS |
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TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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Having observed through a preliminary analysis that the level of nucleotide diversity varies between regions of the cytochrome b gene, we decided to analyze a common fragment in all species. For this purpose, sequences were aligned using ClustalW (THOMPSON et al. 1994) and widely available fragments in the database were selected. Three data sets exploring various ratios of sequence length/number of species were built:
These data sets include members of all major orders of placental mammals. Data set 2, for example, spans 32 families and 9 orders, among which four contain >10 species: Rodentia (66), Chiroptera (24), Eulipothypla (13), and Cetartiodactyla (11). A good representation of the morphological and ecological diversity of mammals is achieved (data available at http://kimura.univ-montp2.fr/data). The taxonomic sampling, for example, spans five orders of magnitude for body mass. Species names were taken from Polymorphix, and higher taxonomic information is from WILSON and REEDER (2005).
Allozyme data:
Estimates of allozyme heterozygosity in 184 mammalian species were obtained from the NEVO et al. (1984) compilation. Thirty species are represented in both the mtDNA and allozyme data set. Allozyme heterozygosities were averaged over >10 (typically 20–30) loci, and the most popular allozyme loci were used in many species. Allozyme heterozygosities are therefore fairly comparable between species.
Sampling quality control:
Polymorphix families are extracted from GenBank and are therefore potentially heterogeneous. In particular, no control of the sampling strategy is made. To address this problem, we checked 60 species randomly chosen from our mtDNA data set. Among the 46 species for which we could access the corresponding publication, 37 (80%) were sampled over their entire geographic range. This proportion was unrelated to taxonomy or body mass. This suggests that these data essentially measure diversity at the species level, as intended.
Polymorphism sequence data analyses:
Two measures of molecular genetic variability were used, namely the nucleotide diversity 
(TAJIMA 1983) and Watterson's statistics 
w (WATTERSON 1975). In the case of the haploid, maternally transmitted mtDNA, both statistics are unbiased estimates of the Nefµ product under the assumption of neutrality and mutation/drift equilibrium, where Nef is the effective population size of females and µ is the locus mutation rate. and w were calculated from the total length of the analyzed fragments and expressed in per-site level of diversity (after being divided by sequence length).
The neutrality index (NI; RAND and KANN 1996) was calculated for data set 1 when outgroups were available. This index aims at comparing the ratio of nonsynonymous (i.e., amino acid changing) to synonymous (silent) changes within species (Pn/Ps) and between species (dn/ds): The NI is 1 when evolution is neutral, >1 under purifying selection, and <1 in case of adaptation. The significance was assessed using the McDonald–Kreitman test (MCDONALD and KREITMAN 1991). Estimates of , w, and NI were obtained using the Bio++ library (DUTHEIL et al. 2006).
Ecological and life-history variables:
For each species in the data set, five life-history traits, eight ecological variables, and The World Conservation Union (IUCN)-threatened species categories (IUCN, 2001) were compiled from multiple published sources (see Table 1 for explanation of variables and http://kimura.univmontp2.fr/data for references). The order, family, and species taxonomical levels were assigned to conform to recent taxonomical assessment (WILSON and REEDER 2005), and a fourth level, namely a supra-order, was assigned following recent molecular phylogenies (MURPHY et al. 2001; SPRINGER et al. 2004). The five life-history variables were (i) body mass, (ii) sexual maturity (age of female sexual maturity in months), (iii) reproduction frequency (time between two litters in months), (iv) maximal longevity (estimating from record longevity in years), and (v) fecundity (number of young per litter). Body mass is defined as the mean of the male and female adult body weights. All the maximal longevity values were retrieved from the AnAge database (DE MAGALHAES et al. 2005). We do not have any information about population structure (i.e., details on how many populations have been sampled) for all species in our data set. Therefore we used the BERLIN et al. (2007) data set. BERLIN et al. (2007) computed FST on the basis of cytochrome b polymorphism data for 30 genera, among which 17 genera match with our data set.
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Statistical analyses:
Genetic diversity measures were arcsine transformed (SOKAL and ROHLF 1981) and analyzed under the general linear model assumptions using R (IHAKA and GENTLEMAN 1996). Quantitative life-history variables were log transformed. Because of the large number of factors, we could not perform a single full analysis. First, the effect of each ecological and life-history variable on genetic diversity was tested using independent regression or one-way ANOVA. Then we tested all combinations of two factors with interaction except for population structure because of the weak sample size (two-way ANOVA, multiple regression, ANCOVA).
Phylogenetic control:
A significant correlation between variables across species can arise just because of their shared phylogenetic history, even if the variables evolve independently (FELSENSTEIN 1985). Phylogeny must therefore be regressed out of the analyses using the so-called comparative methods. Before doing this it must be shown that the variable of interest—in this study, genetic diversity—exhibits significant phylogenetic inertia (e.g., ASHTON 2001). For this purpose, we tested for a taxonomic effect by using supra-order, order, and family as explanatory factors in one-way ANOVAs. Having detected a significant taxonomic effect, we performed a nested-hierarchical ANOVA to optimally decompose the variance across taxonomic levels. We also measured the phylogenetic autocorrelation of genetic diversity using Moran's I statistics (GITTLEMAN and KOT 1990, implemented in APE package, PARADIS et al. 2004).
When significant phylogenetic inertia was detected, we controlled for phylogeny in two ways. First, we used the residuals of the nested-hierarchical ANOVA for reanalyzing the effects of ecological and life-history traits. Second, we employed the phylogenetic eigenvector regression (PVR) method to correct for phylogenetic inertia (DINIZ-FILHO et al. 1998; DESDEVISES et al. 2003). This method can be applied to both continuous and discrete variables. The method starts by performing a principal coordinate analysis on a matrix of between-species patristic distances (implemented in ADE4-R package, CHESSEL et al. 2004). Following DESDEVISES et al. (2003), all the principal coordinates that were significantly correlated to the dependent variable were selected. Traits under analysis were then regressed on the retained eigenvectors. The estimated values express phylogenetic trends in the data, and residuals express independent evolution of each species. The proportion of genetic diversity variance explained exclusively by the ecological and life-history variables was quantified using multiple linear regressions, and its significance was assessed by using a regular parametric F-test (the permutation test used by DESDEVISES et al. 2003 gave similar results). Finally, the contrast method (FELSENSTEIN 1985) was also used on continuous variables, yielding qualitatively equivalent results (not shown).
The phylogenetic tree was manually built according to the literature (MURPHY et al. 2001; HUCHON et al. 2002; ADKINS et al. 2003; HASSANIN and DOUZERY 2003; SPRINGER et al. 2004; STEPPAN et al. 2004; TEELING et al. 2005; tree available as supplemental material at http://www.genetics.org/supplemental/). One sequence per species was randomly chosen to estimate branch lengths using the maximum-likelihood method (PHYML; GUINDON and GASCUEL 2003, model TN93 + 
).
Substitution rate analysis:
The phylogenetic tree was also used to measure lineage-specific evolutionary rates. We performed a molecular clock analysis using the Multidivtime program (THORNE et al. 1998). To get sufficiently accurate estimates, we used only species for which the complete cytochrome b was available (data set 1, 89 species). The Bayesian approach in Multidivtime simultaneously estimates the rate and age for each node of a given tree, assuming a prior distribution of evolutionary rates along branches, and, optionally, constraints on the age of certain internal nodes. We used five fossil calibration points with upper and lower bounds: Cervidae/Bovidae (16.4–23.8 MY, HASSANIN and DOUZERY 2003), Feliformia/Caniformia (23.8–42.8 MY, BENTON and DONOGHUE 2007), Primates/rodents (61.5–95.5 MY, BENTON and DONOGHUE 2007), Pan/Homo (6.5–10.0 MY, BENTON and DONOGHUE 2007), Mus/Rattus (10.0–13.0 MY, BENTON and DONOGHUE 2007). For each species, we stored the relative rate estimated in the corresponding terminal branch of the tree.
The mitochondrial DNA of mammals is characterized by a notoriously high amount of homoplasy. This effect decreases the efficiency of mitochondrial markers for phylogenetic analyses (see SPRINGER et al. 2001; GALEWSKI et al. 2006) and presumably also affects substitution rate estimates. To limit the effect of saturation, we chose to focus on transversions only, which are much less prone to generate homoplasy than transitions.
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RESULTS |
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TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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The mtDNA neutrality index was calculated for 76 species and varied between 0.216 and 26.7. Two-thirds of the mtDNA data sets analyzed showed a NI value >1, which is indicative of a predominant effect of purifying selection. NI was not correlated to any of the life-history and ecological variables analyzed here or to allozyme heterozygosity or taxonomy. No clear pattern emerged that could distinguish the 25 species showing a NI value <1 from a random sample of the data set. This contrasts again with the BAZIN et al. (2006) study in which a significantly lower average NI was reported in (presumably more abundant) invertebrates than (presumably less abundant) vertebrates, in agreement with the genetic draft model. Only two species, Pteronotus parnellii (Chiroptera, P-value = 0.007) and Microcebus rufus (Primates, P-value = 0.024) showed a significantly <1 NI, which is not more than expected just by chance, given the number of independent tests performed. Thirteen species, however, showed a significantly >1 NI. It should be noted that this result is robust to a potential underestimation of the synonymous divergence due to multiple hits; in the case of too distant outgroups, underestimating ds leads to an underestimate of NI.
Overall, these results do not support a prominent role of adaptive evolution in the mitochondrial genome of mammals. Although adaptation of course may occasionally occur, overall patterns of mtDNA diversity across taxa appear compatible with a nearly neutral mode of evolution, in which demographic effects are the major determinants of mtDNA variation. Mammalian species may well belong to Gillespie's "drift zone" (see Figure 1).
Neither life-history traits nor ecology correlate with mtDNA diversity:
Assuming that mtDNA diversity is governed mainly by population size variations, it is expected that the most abundant species would tend to be, on average, the genetically most diverse. Direct estimates of population size are available for a few mammalian species only and involve very large confidence intervals (NEI and GRAUR 1984). We can, however, make use of biological descriptors of species potentially correlated to population size. A total of 14 variables were used to explore as widely as possible the potential determinism of mtDNA diversity in mammals.
Analyses using nucleotide diversity (), Watterson's statistic (w), or synonymous nucleotide diversity (s) and any of the three mtDNA data sets gave similar results. Except when indicated, we present only the results obtained from data set 2 (401 nucleotides, 138 species) using the nucleotide diversity (other results are available on request). The mean per-site nucleotide diversity is 0.025 ± 0.022 (mean synonymous nucleotide diversity: 0.097 ± 0.090). The most variable species is the Southern pocket gopher (Thomomys umbrinus, Geomyidae, Rodentia, = 0.106) and the least variable one is the gray-brown mouse lemur (Microcebus griseorufus, Cheirogaleidae, Primates, = 0.0004).
We first analyzed every explanatory variable separately (Table 2). Among continuous variables, body mass, sexual maturity, and longevity had a significant effect. In spite of the great variability of body mass in the data set (from 3.25 g for the common shrew, Sorex cinereus, to 666.5 kg for the yak, Bos grunniens), this variable explained only 6% of mtDNA polymorphism variability. This result is similar to WOOTEN and SMITH's (1985) allozyme study (r2 = 0.04, P-value = 0.034). Two other continuous variables had a significant effect: sexual maturity (r2 = 0.1252, P-value = 0.0059) and longevity (r2 = 0.1260, P-value = 0.0091). These variables are strongly correlated to body mass (r2 = 0.4254, P-value < 0.0001 for sexual maturity and r2 = 0.4548, P-value < 0.0001 for longevity). The effects of body mass, sexual maturity, and longevity were removed when phylogenetic inertia was controlled for (see Table 2), indicating that the influence of life-history variables on mtDNA genetic diversity, if any, is very low.
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We detected a positive correlation between genetic diversity and FST (P-value = 0.02, Kendall no parametric test). This correlation, however, is largely explained by a higher average FST in rodents. It was removed by a taxonomic control (P-value = 0.1263). Moreover, we did not find any correlation when we used the total BERLIN et al. (2007) data set (including genera missing in our data set, N = 30).
Then we considered every two-factor combination of the explanatory variables. We present the result only for several models (Table 3; detailed results available on request). In two-way ANOVAs, no significant effect was found, except the body mass effect in one analysis, which did not resist the phylogenetic control (see Table 2).
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= 0.033). Carnivora is the least polymorphic order represented by more than one species in the data set (average = 0.008, Figure 4). Supra-order average levels of diversity are also significantly different from each other, Euarchontoglire species being more diverse than Laurasiatheria. Similarly, we calculated the phylogenetic autocorrelation using Moran's I statistic (GITTLEMAN and KOT 1990) and the phylogenetic inertia using PVR (DINIZ-FILHO et al. 1998; DESDEVISES et al. 2003). Genetic diversity had a highly significant autocorrelation (I = –0.01943, P-value < 0.0001) and the PVR method indicated a strong phylogenetic inertia on this variable (r2 = 0.319, P-value < 0.0001, after 10,000 random permutations). This explains why the few significant effects of ecological and life-history traits that we detected vanished when phylogenetic inertia was controlled for.
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This hypothesis predicts that the average genetic diversity of taxonomic groups should be correlated with their current mutation rates. The mutation rate is usually unknown, but can be approached by estimating lineage-specific substitution rates; under neutrality, the two are proportional. We found that species' genetic diversity was positively correlated to their relative transversion substitution rate as estimated with Multidivtime (r2 = 0.110, P = 0.0016; Figure 5). This result is robust to the removal of non-neutral first and second codon positions (r2 = 0.044, P = 0.048) and to a taxonomic control—i.e., the average family rate is correlated to the average family diversity (N = 22, P = 0.04, Kendall test). Our mtDNA substitution rate estimator explains only 11% of the variance of mtDNA diversity across species, which can be explained by the high variability in genetic diversity resulting from demographic (or selective) stochasticity and/or by inaccurate estimation of evolutionary rates due to saturation and incomplete fossil information.
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DISCUSSION |
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TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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The claim of a prominent role for adaptive evolution in animal mtDNA is therefore not supported at the Mammalia level: mtDNA diversity is correlated to allozyme diversity, and neutrality indices mostly support purifying selection. Genetic drift, not genetic draft, is probably the main determinant of species' genetic diversity in this group. This can be considered good news for users of mtDNA as a demographic marker in mammals. Although the occurrence of occasional adaptive events cannot be excluded, mammalian mtDNA appears little affected by frequent selective sweeps. The question is difficult to assess in other vertebrate taxa because their ecology and life history have not been studied as deeply as in mammals. Fish, for example, in which larger population sizes are expected and for which the mtDNA diversity apparently does not correlate to the nuclear one (BAZIN et al. 2006), could be worth investigating. Birds are also interesting because of their weaker average mtDNA diversity (as compared to mammals), perhaps due to the linkage between mtDNA and the W chromosome (BERLIN et al. 2007).
Given this result, it came as a surprise that we could not detect an effect of potential population size indicators on mtDNA genetic diversity. Of course, it is possible that the life-history and ecological variables that we used are not appropriate markers of species effective population size. But this would mean that species abundance is not correlated to body size, geographic range, IUCN categorization, or to any combination of these and other variables, which seems quite unlikely. The relationship between body mass and abundance, for example, is well supported in many groups (WHITE et al. 2007), including mammals (DAMUTH 1987). BAZIN et al. (2006) detected a significant effect of indicators of population size on allozyme heterozygosity using much smaller data sets and arguably less sophisticated variables (marine vs. terrestrial mollusks, "large" vs. "small" crustaceans).
Similarly, the results obtained by MULLIGAN et al. (2006) are difficult to explain by a population size effect. We agree that the order showing the greatest mtDNA and allozyme variability (Rodentia) is one with large expected populations, whereas the least polymorphic order (Carnivora) is predicted to include species with smaller populations (higher-order predators). The ranking of orders with intermediate levels of diversity, however, is difficult to reconcile with intuition about populations sizes: Artiodactyla and Cetacean species are more polymorphic, on average, than Chiroptera and Eulipotyphla. It is interesting to note, finally, that Rodentia is the fastest-evolving mammalian order and Carnivora one of the slowest evolving (Multidivtime analysis; results not shown), which is in agreement with our mutation-effect hypothesis. Finally, BERLIN et al. (2007) reported a significant correlation between body mass and mitochondrial diversity in birds and mammals. They did not, however, perform any phylogenetic control. When we did so using their data, the body mass effect was removed, as in this study.
The detection of a mutation rate effect but no population size effect suggests that this pattern is due to a strong stochasticity of population size in mammals. Generalizing NEI and GRAUR (1984), IIZUKA et al. (2002) showed that when population size randomly fluctuates between two distinct values, the mutation rate becomes the major determinant of genetic diversity (for a small-enough minimal population size). A metapopulation model with local extinction and recolonization also predicts that diversity becomes independent from effective population size when the extinction rate is higher than the migration rate (PANNELL and CHARLESWORTH 1999). The literature provides examples of population size fluctuations caused by global climatic changes, for example, during the past 3 million years (HEWITT 2000), or by pandemic diseases (HARDING et al. 2002). Our results suggest that stochastic variations in effective population size are probably a general process of mammalian species dynamics, strong enough to remove any effect of (current) species abundance on mtDNA diversity.
This conclusion is apparently in conflict with previous reports of ecological/life history correlates of nuclear genetic diversity. NEVO et al. (1984) conducted a meta-analysis of allozyme data and reported a significant effect of six variables (including range size, habitat, and longevity) on allozyme heterozygosity in mammals. These are only a few of the many ecological and life-history variables that they used, however. The percentages of explained variance were low and similar to those that we report in this study, and no phylogenetic control was performed. We reanalyzed the allozyme data controlling for taxonomy. Of the 21 variables considered by NEVO et al. (1984), 6 significantly influence allozyme diversity, among which 5 are still significant after taxonomic control: geographic range size, specialist vs. generalist, aridity, species size, and young dispersal; only 1 effect (longevity) was removed. The allozyme results appear more robust to taxonomical control than mitochondrial ones. We see two potential explanations for this pattern. First, allozyme heterozygosity is obtained by averaging over several loci, thus reducing the variance of the coalescent process. Second, mammalian mitochondrial DNA could occasionally experience selective sweeps, although we did not detect any NI effect. Although NEVO et al. (1984) put the emphasis on the detected correlations, our view is that this study is largely consistent with ours in suggesting a weak, if any, influence of ecology and life history on genetic diversity in mammals.
One conflict between mtDNA and nuclear data that we consider significant is the IUCN status effect. SPIELMAN et al. (2004) reported that the nuclear heterozygosity of threatened taxa is, on average, lower than that of nonthreatened relatives. The effect is rather strong in mammals, in which 84% of endangered species are less diverse than their nonendangered relatives. This is true for both allozymes and microsatellite markers, and this contrasts with our mtDNA results. Even by applying the pairwise approach used by SPIELMAN et al. (2004), we failed to recover any effect of the IUCN status: <50% of the endangered species in our mtDNA data set are less polymorphic than their nonendangered relatives. This could be due to a lack of power: our data set includes only 22 endangered species (63 in SPIELMAN et al. 2004) and relies on a single locus, the mitochondrial one, while nuclear estimates of diversity are obtained by averaging over several loci, thus reducing the variance of the coalescent process. The mtDNA mutation rate effect that we detect, moreover, might add some noise and further decrease the power of the analysis.
So, even in the absence of strong adaptive effects, mtDNA diversity in mammals is largely unpredictable knowing species biology, and probably reflects in the first place the product of the mitochondrial mutation rate by the time elapsed since the last event of diversity reduction. This does not preclude the use of mtDNA to infer past demographic history, but still suggests that mtDNA diversity is a poor indicator of current population size and health.
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ACKNOWLEDGEMENTS |
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TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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LITERATURE CITED |
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TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
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