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Proc Biol Sci. Jan 7, 2007; 274(1606): 143–150.
Published online Oct 31, 2006. doi:  10.1098/rspb.2006.3639
PMCID: PMC1679881

Quantitative measure of sexual selection with respect to the operational sex ratio: a comparison of selection indices


Despite numerous indices proposed to predict the evolution of mating systems, a unified measure of sexual selection has remained elusive. Three previous studies have compared indices of sexual selection under laboratory conditions. Here, we use a genetic study to compare the most widely used measures of sexual selection in natural populations. We explored the mating and reproductive successes of male and female bank voles, Clethrionomys glareolus, across manipulated operational sex ratios (OSRs) by genotyping all adult and pup bank voles on 13 islands using six microsatellite loci. We used Bateman's principles (Is and I and Bateman gradients) and selection coefficients (s′ and β′) to evaluate, for the first time, the genetic mating system of bank voles and compared these measures with alternative indices of sexual selection (index of monopolization and Morisita's index) across the OSRs. We found that all the sexual selection indices show significant positive intercorrelations for both males and females, suggesting that Bateman's principles are an accurate and a valid measure of the mating system. The Bateman gradient, in particular, provides information over and above that of other sexual selection indices. Male bank voles show a greater potential for sexual selection than females, and Bateman gradients indicate a polygynandrous mating system. Selection coefficients reveal strong selection gradients on male bank vole plasma testosterone level rather than body size.

Keywords: Clethrionomys glareolus, mating system, testosterone, opportunity for sexual selection, Morisita index, index of resource monopolization

1. Introduction

Sexual selection theory was developed to explain the evolution of sexually dimorphic characters (Darwin 1859, 1871) and is widely used to explain the evolution of mating systems (Shuster & Wade 2003). In turn, mating systems also influence sexual selection (Andersson 1994). However, there is no unified agreement in the literature as to the best quantitative measure that provides a direct relationship between sexual selection and the mating system, allows the possibility of cross-taxonomic comparative analyses and can be used in quantitative genetic theory (Arnold & Duvall 1994). Up to this point, the different quantitative measures of a mating system had not been rigorously tested. Recently, Kokko et al. (1999) emphasized that a unique ‘best’ measure is not available and advocated the use of several measures, whereas comparative studies on experimental populations recommended Morisita's index (Fairbairn & Wilby 2001) or Bateman's principles (Wade 1979; Jones et al. 2000, 2002, 2004, 2005).

Bateman's first two principles are based on the standardized variance in either the number of mates that sire or bear progeny (mating success) or the total number of offspring sired (reproductive success) and indicate the maximum strength on sexual selection acting in a population (Bateman 1948). Bateman's variances were formulated quantitatively as the opportunity of sexual selection (Is) and selection (I), respectively (Crow 1958; Wade 1979; Wade & Arnold 1980). However, two alternative indices that measure mate or resource acquisition were proposed: the index of resource monopolization (Q; Green 1966; Ruzzante et al. 1996), which measures the observed variance as a fraction of the maximum possible variance corrected by the variance when acquisition is equal; and the Morisita index (Iδ; Morisita 1962) which is similar to Q, but is not expressed as a fraction of the maximum variance. Bateman's third principle, the sexual selection gradient, defined recently as the Bateman gradient (Andersson & Iwasa 1996), is the statistical relationship between mating and reproductive successes approximated by a regression line (Arnold & Duvall 1994). Alternative measures of sexual selection include selection differentials (s′) and selection gradients (β′) that measure the direct selection on phenotypic characters to reveal the target(s) of sexual selection (Lande & Arnold 1983). These coefficients quantify the intensity of sexual selection and have greater predictive value in relation to evolutionary change; however, they cannot be used for cross-taxonomic comparisons owing to their dependency on specific phenotypic traits.

Fairbairn & Wilby (2001) recently compared the different quantitative measures of sexual selection in laboratory populations of mealworm beetles, Tenebrio molitor, at different operational sex ratios (OSRs) and densities. Sexual selection on male traits is predicted to covary with the OSR, or the proportion of sexually active males to fertilizable females at any one time (Emlen & Oring 1977; Clutton-Brock & Parker 1992), and is supported with empirical data (e.g. Fleming & Gross 1994; Kvarnemo 1994; Mills & Reynolds 2003). Fairbairn & Wilby (2001) questioned the validity of Is and I, particularly in populations with female-biased sex ratios and recommended using Morisita's index. However, comparisons of experimental rough-skinned newt, Taricha granulosa, populations at two OSRs and sex-role reversed pipefish, Syngnathus typhle, populations at three OSRs concluded that Bateman's principles, in particular the Bateman gradient, are the best measures of sexual selection and mating systems (Jones et al. 2004, 2005).

In this paper, we empirically test the different quantitative measures of sexual selection by manipulating OSR in natural populations of the bank vole, Clethrionomys glareolus. Although bank voles serve as a model species for many different purposes (e.g. Koskela et al. 1998; Oksanen et al. 2002; Mappes & Koskela 2004), experimental data studying sexual selection in natural populations are lacking. Although two studies have analysed paternity using molecular techniques (Sikorski & Wójcik 1990; Ratkiewicz & Borkowska 2000), only one found evidence of multiple paternity in natural populations (Ratkiewicz & Borkowska 2000). In Central Finland, reproduction takes place from May to mid-September, during which time up to four litters ranging from 2 to 10 pups (5.27±1.32, mean±s.e.) can be born (Koivula et al. 2003). Males provide no care for the young or the mother and except for a brief period following mating (‘time out’, cf. Ahnesjö et al. 2001), they are always able to mate once mature. However, females are in oestrus for only 1–2 days following birth and their 21 day period of gestation further shortens the period when they are able to mate (‘time in’ cf. Ahnesjö et al. 2001). As such, even though the primary sex ratio is equal, we predict that the potential for a male-biased OSR in natural bank vole populations is high.

We report the results of an experiment in which we measured male parameters, body mass and plasma testosterone level, and manipulated OSR in natural populations of C. glareolus in order to determine its (genetic) mating system and compare the measures of sexual selection using Is, I, Qmatingsuccess(ms), Qreproductivesuccess(rs), Iδ-matingsuccess(ms), Iδ-reproductivesuccess(rs), Bateman gradient and selection coefficients, s′ and β′.

2. Material and methods

(a) Animals and collection of samples

Nineteen islands situated on Lake Konnevesi, Finland (62°37′ N, 26°20′ E) were suitable owing to their size, ranging from 0.32 to 2.48 ha and their accessibility for trapping. The islands were live trapped in May 2002 for a period of 4 days and all the small mammals were removed from the islands.

Thirty-eight adult female and fifty-six adult male bank voles were selected from wild-caught bank voles captured in Konnevesi. All the animals used in the experiment were of proven fertility; each had sired or given birth to at least one litter in the laboratory. Body mass (g) and head width (±0.1 mm) were measured for all the animals, individually marked, prior to release. Male tissue (2 mm in diameter) was stored at −70°C to be used in paternity analyses. A 75 μl intra-orbital blood sample was taken (see methods in Oksanen et al. 2003) for testosterone analysis from all the males 3 days prior to release.

Females and males were randomly assigned to groups corresponding to the 19 islands. The groups contained two females, with the number of males varying between 2, 3 or 4 to create OSRs of 1, 1.5 and 2, which were released to seven, six and six islands, respectively, with no effect of island size on OSR distribution (one-way ANOVA, F2,19=0.451, p=0.72). Our mean±s.e. population density (5.95±0.63 individuals per hectare) corresponds to the natural density during the breeding season for these islands (9.28±2.67 individuals per hectare; Hakkarainen et al. in press). The groups were released onto the islands on 27 June 2002. After a period of three weeks, each island was live trapped, twice daily, for 4 days, using Uggland special multiple-capture live traps baited with oats and potatoes. The trap density was 25 traps per hectare spaced ca 20 m from each other. This trapping procedure has proved effective in trapping all the bank voles from small island populations (T. Mappes & E. Koskela 1999, personal communication). All the females were brought to the laboratory to give birth in order to record their litter size. The pups were individually marked and tissue samples stored at −70°C for paternity analysis. All the pups were returned to the islands with their mothers within 4 days of their birth.

(b) Laboratory procedures and microsatellite genotyping

Total genomic DNA was extracted using a solution of 5% chelex resin (Sigma; Pearce et al. 1997). Individuals were genotyped at six microsatellite loci, MSCg 04, 07, 09, 15, 18 and 24, respectively (Gockel et al. 1997). The amplifications were carried out in a total volume of 10 μl, with the use of 75 mM Tris–HCl, 1.25 mM MgCl2, 20 mM (NH4)2SO4, 0.01% Tween 20, 5 pmoles of each primer (1/10 of one of the two primers labelled with either IDR-700 or IDR-800 fluorescent dye), 200 μM of each dNTPs, 0.5 unit Taq polymerase (Gibco-BRL) and 20–50 ng DNA. Amplification mixes were subjected to a denaturation step at 94°C for 5 min followed by 30 cycles at 94°C for 30 s, 55°C for 30 s and 72°C for 45 s, followed by an elongation step at 72°C for 5 min. Products of amplifications were run in a LiCor automatic sequencer. Alleles were scored by eye and the size was determined by running the sequence of the plasmid pUC18.

(c) Paternity assignment

Likelihood-based analysis of paternity was conducted with the software Cervus v. 2 (Marshall et al. 1998). The following simulation parameters were used: 10 000 cycles, 100% of candidate parents sampled, 100% of loci typed and a genotyping error rate of 1%. We used the ‘one parent known’ option in Cervus to assign paternity. All the males on the same islands (2–4) were included as candidate fathers. We accepted paternity assignment for the candidate with the highest LOD score at confidence level of 95% and with no mismatches (128 of 140 assignments, 91%). Only 12 pups remained unassigned (9%).

(d) Testosterone (T) assay

Plasma T was measured using a radioimmunoassay kit (TESTO-CTK, DiaSorin, Byk-Sangtec Diagonstica GmbH & Co, Germany). Fifty microlitres of the seven standards or 20 μl of the blood plasma samples were added with 500 μl of 125I-labelled T to tubes coated in a T antiserum. During the 3 h reaction period at 37°C, labelled T and sample or standard T competed for a fixed number of antibody-binding sites. After aspiration of the mixture, the radioactivity of the tubes was measured in a gamma counter and is inversely related to the amount of unlabelled T in the samples and the standards. Sample T concentration was determined by interpolation from the standard calibration curve and corrected by ((50/20)×(550/520)). We screened plasma from C. glareolus for parallelism with the kit's standard curve using a series of six dilutions. The dilutions run parallel to the standard curve (homogeneity of slopes for sample versus standard ANCOVA: F1,22=2.269, p=0.148), thus validating the use of this kit in bank voles. This technique also enabled us to determine that pooled vole plasma samples measured without dilution correspond to 50% of antibody bound. We found that this kit is also highly repeatable for bank voles (r=0.961, n=26, p<0.01).

(e) Selection measures

Our molecular paternity analysis enabled us to determine the bank vole genetic mating system, defined as the distribution of biological parentage in a population (Jones et al. 2005), by estimating the number of genetic mates (mating success) and genetic offspring (reproductive success; Jones et al. 2004).

Bateman's first and second principles were calculated following the methodology of Wade (1979) and Wade & Arnold (1980),


where X¯ and σ2 are the mean and the variance in either mating or reproductive success for the opportunity for sexual selection (Is) and selection (I), respectively.

Bateman's third principle: the Bateman gradient, βss, was determined by the least-squares regression of reproductive success on mating success and is the slope of the regression. Differences between Bateman gradients were examined using the homogeneity of regression slope test in ANCOVA (Field 2005).

Selection coefficients on phenotypic characters were measured using the techniques developed by Lande & Arnold (1983). Phenotypic measurements were log transformed and standardized to have a mean of 0 and a variance of 1 before analysis. Directional selection differentials (s′) are calculated as the covariances between fitness and each trait, and the selection gradients (β′) are estimated from the linear multiple regression coefficients of fitness on the traits (Lande & Arnold 1983).

Index of resource monopolization (Q) is calculated following the theory of Green (1966) and Ruzzante et al. (1996),


where X¯ and σ2 are the mean and the variance in either mating or reproductive success for Qms and Qrs, respectively, and n is the number of individuals.

The Morisita index (Iδ) is calculated from Morisita (1962),


where x is the individual mating or reproductive success for Iδ-ms and Iδ-rs, respectively.

(f) Statistics

ANCOVA was carried out with Is, I, Qms, Qrs, Iδ-ms and Iδ-rs as dependent variables, OSR as a fixed variable and density (individuals per hectare) as a covariate. Contingency tables were calculated following Siegel & Castellan (1988).

3. Results

Of the 38 females released on 19 islands, six from six islands were not re-caught. As a result, we excluded those islands that lacked the original number of founder individuals from further analyses. All the 26 females on the remaining 13 island populations gave birth and 140 pups were analysed for paternity from 42 males. Of these 26 litters, 13 had a single sire and 13 had multiple sires. All males at an OSR of 1 were successful in mating, whereas 33 and 38% of males failed to sire any pup at the OSRs of 1.5 and 2, respectively (figure 1). Male mating success is only statistically different from that of females at an OSR of 2 (contingency χ2-tests, OSR=1: χ22=0.07, p=0.97; OSR=1.5: χ22=3.33, p=0.19; OSR=2: χ32=9.53, p=0.023; figure 1).

Figure 1
Distributions of genetically documented mating events for male and female bank voles from 13 island populations at OSRs of (a) 1, (b) 1.5 and (c) 2. Black bars, males; Grey bars, females.

(a) Effect of operational sex ratio on sexual selection based on mating success: Is, Iδ-ms and Qms

Estimates of the opportunity for sexual selection (Is), the Morisita index (Iδ-ms) and the index of resource monopolization (Qms) are shown in figure 2a,c,e. For males, opportunities for sexual selection, Is, Iδ-ms and Qms, closely resemble each other, but although they appear higher at an OSR of 1.5, there was no significant effect of OSR on any estimate (ANCOVA, Is : F2,12=0.085, p=0.920; Iδ-ms : F2,12=0.007, p=0.993; Qms : F2,12=1.040, p=0.402).

Figure 2
Sexual selection measures for bank voles from 13 island populations at OSRs of 1, 1.5 and 2: (a,b) Is and I, the opportunity for sexual selection and selection; (c,d) Iδ-ms and Iδ-rs, the Morisita indices for mating and reproductive success ...

In females, there was neither an obvious visual trend (figure 2a,c,e) nor a significant effect of OSR on the estimates of sexual selection (ANCOVA, Is : F2,12=0.600, p=0.575; Iδ-ms : F2,12=1.129, p=0.376; Qms : F2,12=2.291, p=0.172).

(b) Effect of operational sex ratio on selection based on reproductive success: I, Qrs and Iδ-rs

The estimates of the opportunity for selection (I), the Morisita index (Iδ-rs) and the index of resource monopolization (Qrs) are shown in figure 2b,d,f. For males, opportunities for sexual selection, I, Iδ-rs and Qrs, again closely resemble each other and appear higher at OSRs of 1.5 and 2, but there was no significant effect of OSR on any estimate (ANCOVA, I : F2,12=0.180, p=0.839; Iδ-rs : F2,12=0.365, p=0.707; Qrs : F2,12=0.735, p=0.513).

However, in females, we did find a significant effect of OSR. For the estimates of I and Qrs, we found a significant interaction between OSR and density (ANCOVA, OSR×density, I : F2,12=6.920, p=0.022; Qrs : F2,12=8.599, p=0.013). For both estimates, Bonferroni-corrected post hoc tests revealed that sexual selection in females was the greatest at an OSR of 1 compared with the OSRs of both 1.5 and 2 (p<0.01; figure 2b,f). For Iδ-rs, we found a non-significant interaction trend between OSR and density (ANCOVA: F2,12=4.151, p=0.065). Bonferroni-corrected post hoc tests revealed that sexual selection in females was greater at an OSR of 1 compared with 2 (p=0.025; figure 2d). Although significant effects of OSR on female selection were found, these results should be interpreted cautiously, as variances were calculated using only two females per island.

We calculated two-tailed Pearson's correlation coefficients between Is, Qms and Iδ-ms, and between I, Qrs and Iδ-rs for males and females separately. All of the measures are significantly positively intercorrelated (table 1).

Table 1
Pearson's correlation coefficients (two-tailed) between the different indices of sexual selection based on mating and reproductive successes. (Is and I, the opportunity for sexual selection and selection; Qms and Qrs, the index of monopolization and ...

(c) Effect of operational sex ratio on the Bateman gradient

Bateman gradients showed that the reproductive success of males increased significantly with the number of females with which a male sired young (figure 3). However, for females, reproductive success does not increase significantly with the number of males that sired their young and the females' slopes do not differ significantly from 0 (figure 3). There are no significant differences between the gradients of either the male or the female across the OSRs (ANCOVA, all p>0.3); however, male gradients are significantly steeper than the female gradients at OSRs of 1.5 and 2 (homogeneity of slopes using ANCOVA, sex×mating success: OSR=1.5: F1,19=34.23, p=0.017, OSR=2: F1,35=34.39, p<0.001, OSR=1: F1,11=10.08, p=0.108).

Figure 3
A plot of reproductive success versus genetic mating success for bank voles, showing the Bateman gradient for males (black points and solid lines) and females (grey points and dashed lines) at different OSRs. Filled circle, OSR=1: y=3.667x−2; ...

(d) Effect of operational sex ratio on selection coefficients, s′ and β

At an OSR of 1.5, both selection coefficients (s′ and β′) with respect to male reproductive success showed that sexual selection acted significantly on a male's plasma testosterone (T; table 2). Similar, but non-significant, trends were found with respect to genetic mating success at an OSR of 1.5, revealing that sexual selection also acts on T (table 2).

Table 2
Estimates of the coefficients of sexual selection, selection differentials (s′) and selection gradients (β′) on body mass and testosterone levels of males at different operational sex ratios. (In both the analyses, relative fitness ...

A simple linear regression on unstandardized data between T and reproductive success (the total number of pups sired) revealed a significantly positive relationship (simple linear regression for all OSRs pooled together: F1,37=11.95, p=0.001, R2=0.25). Unfortunately, with the present sample size, we failed to find a significant effect of OSR on the regression equations (homogeneity of slopes using ANCOVA, OSR×T: F1,37=0.529, p=0.472; figure 4). A significant linear regression was also found between T and the total number of genetic mates (simple linear regression for all the OSRs pooled together: F1,37=6.61, p=0.014, R2=0.16); however, again, no significant differences were found between the regression equations at different OSRs (homogeneity of slopes using ANCOVA, OSR×T: F1,37=1.63, p=0.21).

Figure 4
The plasma testosterone level (unstandardized and untransformed) of male bank voles and their reproductive success (number of pups sired) at different OSRs. Filled circle, OSR=1: y=0.693x−0.134; R2=0.54, N=6, p=0.094. Filled square, OSR=1.5: ...

4. Discussion

Only three previous studies have experimentally compared different measures of sexual selection with OSR, yet in both experiments, laboratory or artificial populations were used (Fairbairn & Wilby 2001; Jones et al. 2004, 2005). Our results provide an empirical test of the widely used measures of selection using experimental populations of the bank vole, C. glareolus, in natural habitats at three manipulated OSRs.

(a) Comparison between sexual selection and selection indices: Is, I, Qms, Qrs, Iδ-ms and Iδ-rs

All indices agreed that selection on females, based on I, Qrs and Iδ-rs, was the highest at an OSR of 1 (figure 2b,d,f) and that there was no evidence for an effect of OSR on sexual selection in males or females. We also show significant positive correlations between all indices of selection (table 1) and as such, we find that sexual selection and selection estimates covary with OSR in a similar manner.

However, Ruzzante et al. (1996) and Blanckenhorn et al. (1998) showed that when either the number of resources per competitor or the number of mates differs between populations, Q is a better measure of sexual selection than I. Even though the relative number of mates differed between our island populations, we found that all selection estimates based on Q and I show positive intercorrelations. Populations with female-biased sex ratios is another situation in which the validity of I has been questioned and in this case, the Morisita index is preferred (Fairbairn & Wilby 2001). However, as natural bank vole populations are male biased, our experiment did not include islands with female-biased sex ratios; therefore, we are unable to corroborate the results of Fairbairn & Wilby (2001). In terms of our study system and the OSR manipulations we carried out, we agree with Jones et al. (2004, 2005) that the use of Is and I as measures of sexual selection is justified.

Sexual selection on male traits is predicted to be the strongest when there is intense competition for females, such as when the OSR is biased towards males (Emlen & Oring 1977). Although figure 2b,d,f suggests that sexual selection in males is higher at the male-biased OSRs of 1.5 and 2, we found no significant differences in sexual selection estimates between OSRs in male bank voles. A primary sex ratio of 1 : 1 may already provide a sufficiently male-biased OSR, thus increasing the number of males has only a small effect on the intensity of sexual selection. In terms of females, even though the population sizes used are biologically relevant (Hakkarainen et al. in press), only two females were used per island; therefore, we will not draw any detailed conclusions concerning female bank vole genetic mating system in this paper. Nevertheless, at an OSR of 1, female selection estimates are high (figure 2b,d,f) yet they cannot be attributed to benefits of multiple mating, as number of mates has no effect on litter size (figure 3) and there is no evidence for sexual selection (Arnold & Duvall 1994). Therefore, another aspect of fitness is increasing the variance in female reproductive success and one such trait may be fecundity selection.

(b) Bateman gradient

The slope of the Bateman gradient reveals the potential for sexual selection. In bank voles, the regression of fecundity on mating success is always steeper for males than females, thus males have a greater potential for sexual selection (figure 3). Selection estimates from the quantitative indices, Is, I, Qms, Qrs, Iδ-ms and Iδ-rs, also showed higher sexual selection in males (figure 2). However, Bateman gradients further reveal that in females, fecundity reaches an asymptote after one mating. As females receive no provisioning from males, we can conclude that females experience no gain in fecundity once they secure a single mate. Thus, sperm from one male is sufficient to fertilize all their litter.

Our results lead us to expect a polygynandrous mating system in bank voles (Searcy & Yasukawa 1995). An analysis of all 26 litters reveals that 50% were sired by multiple fathers, a value higher than 0 and 35.5% previously reported (Sikorski & Wójcik 1990; Ratkiewicz & Borkowska 2000), and as many as three fathers sired litters at an OSR of 2 (16.7% of 12 litters). Owing to overlapping ejaculates, male–male competition may therefore be as intense at the ejaculate, as at the population level. Post-mating selection is clearly an important factor influencing male reproductive success in bank voles. Numerous mechanisms have been proposed to explain multi-male mating including: direct non-genetic benefits (Dewsbury 1979; Klemme et al. in press); genetic benefits (Jennions & Petrie 2000) including bet hedging in the presence of density cycles, genotype by environment interaction and ontogenetic conflict (Mills et al. in press); prevention of inbreeding (Zeh & Zeh 1997); and confusion of paternity to deter infanticide (Wolff & Macdonald 2004).

(c) Selection coefficients, s′ and β

A steep Bateman gradient results in persistent directional selection on mating success and any trait correlated with mating success (such as a secondary sexual character) will be under strong selection (Jones et al. 2002). Sexual dimorphism is common in mammals, with males the larger sex, owing to their advantage in gaining access to receptive females (e.g. McElligott et al. 2001). However, in the bank vole, selection coefficients reveal that sexual selection is acting on plasma testosterone level (T) rather than body size (table 2) and T is not correlated with either body mass (Pearson's correlation: r (40)=0.09, p=0.564) or head width (r (40)=0.22, p=0.182). We find evidence for strong selection on T (β′=0.97; table 2), which is likely to affect male mating success through its potential influence on both intra- and inter-sexual selection. In terms of intra-sexual selection, male bank voles implanted with exogenous T had larger home range sizes and sired more offspring than saline implanted males (Mills et al. in preparation b). T also plays an important role in spermatogenesis (mice and rats: Singh & Handelsman 1996; Spaliviero et al. 2004; Sriraman et al. 2004); therefore, it may also be acting on internal male reproductive traits such as sperm characteristics. The role of T in inter-sexual selection is evident through female preferences for dominant males based on cues in their urine (Horne & Ylönen 1996; Kruczek 1997), and the preputial gland, the main source of male sexual attractants, is T-dependent (Radwan et al. 2006).

The strong selection gradient on T (table 2) coupled with significant heritability of T (Mills et al. in preparation b) is predicted to drive high T levels to fixation (Charlesworth 1987). However, the presence of both considerable environmental sources of variation (e.g. population density cycles; Hanski et al. 1993) and genotype by environment interactions (Mills et al. in press) may maintain additive genetic variation for T in bank voles. Furthermore, genetic variation may also be maintained by the tradeoff between T and immune function, as T is predicted to have an immunosuppressive effect due to the negative feedback within and between the endocrine and immune systems (Folstad & Karter 1992). As both the endocrine and immune systems have high metabolic demands immunosuppression may represent adaptive resource allocation, where resources are redirected away from an immune response towards sexual behaviour (Wedekind & Folstad 1994). This tradeoff in bank voles has concomitant effects on both survival and reproductive success (Mills et al. in preparation a).

In light of our results, which highlight that the different indices provide comparable sexual selection estimates, we agree with Jones et al. (2004, 2005) and that Bateman's principles are a valid measure for the characterization of mating systems. The Bateman gradient, in particular, provides not only a sexual selection estimate that can be used for cross-taxonomic comparisons, but also a more thorough description of male and female mating systems.


We acknowledge Maria Tuittu for carrying out genetic analyses, Antti Poikonen and Raimo Saunanen for island fieldwork and Tanja Poikonen for laboratory work. We thank Adam Jones for providing helpful advice and Leena Lindström and Dominique Mazzi for their comments on the manuscript. The study was financially supported by the Centre of Excellence for Evolutionary Ecology at the University of Jyväskylä and the Academy of Finland (grant no. 103508 and 108566 to S.C.M.; 63789, 202166 and 206091 to T.M.; 100143, 78777 and 103148 to E.K.)


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