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Evolution, 58(3), 2004, pp. 608–618 CAN INTRASPECIFIC COMPETITION DRIVE DISRUPTIVE SELECTION? AN EXPERIMENTAL TEST IN NATURAL POPULATIONS OF STICKLEBACKS DANIEL I. BOLNICK Section of Evolution and Ecology, Center for Population Biology, Storer Hall, University of California, Davis, California 95616 E-mail: [email protected] Abstract. Theory suggests that frequency-dependent resource competition will disproportionately impact the most common phenotypes in a population. The resulting disruptive selection forms the driving force behind evolutionary models of niche diversification, character release, ecological sexual dimorphism, resource polymorphism, and sympatric speciation. However, there is little empirical support for the idea that intraspecific competition generates disruptive selection. This paper presents a test of this theory, using natural populations of the three-spine stickleback, Gasterosteus aculeatus. Sticklebacks exhibit substantial individual specialization associated with phenotypic variation and so are likely to experience frequency-dependent competition and hence disruptive selection. Using body size and relative gonad mass as indirect measures of potential fecundity and hence fitness, I show that an important aspect of trophic morphology, gill raker length, is subject to disruptive selection in one of two natural lake populations. To test whether this apparent disruptive selection could have been caused by competition, I manipulated population densities in pairs of large enclosures in each of five lakes. In each lake I removed fish from one enclosure and added them to the other to create paired low- and high-population-density treatments with natural phenotype distributions. Again using indirect measures of fitness, disruptive selection was consistently stronger in high-density than low-density enclosures. These results support long-standing theoretical arguments that intraspecific competition drives disruptive selection and thus may be an important causal agent in the evolution of ecological variation. Key words. minima. Competitive speciation, fitness function, Gasterosteus aculeatus, individual specialization, stable fitness Received June 3, 2003. Accepted October 8, 2003. Classical ecological theory claims that population density will grow to the point where intraspecific competition reduces individuals’ survivorship and/or fecundity. The population density reaches an equilibrium when, on average, each individual can only garner enough resources to produce one surviving offspring. While the population size is at an equilibrium, its genetic make-up may not be, as natural selection will favor genotypes that exceed the average reproductive rate. Such genotypes may capture a disproportionately large share of the limiting resources; use their existing resource income more efficiently to produce offspring; or use novel and exclusive resources, thereby escaping intraspecific competition. This third effect formed the core of Darwin’s explanation of why a population might evolve to use a broader array of resources (Darwin 1859, p. 113). In the latter half of the 20th century, theoreticians formalized this idea that intraspecific competition favors increased ecological and genetic variation (Ludwig 1950; Levene 1953; Dempster 1955; Lewontin 1955; Li 1955; Levins 1962, 1963; Maynard Smith 1962). More recent theory has emphasized the importance of stable underdominance (Wilson and Turelli 1986) or disruptive selection (Dieckmann and Doebeli 1999) in driving this process. Competitive disruptive selection is an example of a more general and somewhat counterintuitive theory of stable fitness minima (Abrams et al. 1993). One way to understand this effect is to visualize the fitness landscape for a population. The classical view of a fitness landscape is of an unchanging topography in which every phenotype has a specific fitness, indicated by the height of the landscape at the point corresponding to that phenotype (Wright 1932). For example, a unimodal resource distribution would produce a single peak in the fitness landscape: the phenotype that can most effi- ciently use the most abundant type of resource has the highest fitness, and the population should evolve toward this optimal phenotype. In contrast to this static fitness landscape, density and frequency dependence results in a dynamic landscape: a fitness ‘‘sphagnum bog’’ (Rosenzweig 1978). Sphagnum bogs consist of a floating mat of vegetation, often of varying thickness, which can be depressed below the water surface by any weight set on it. In this metaphor, the thickness of the mat at any point indicates the carrying capacity of the corresponding phenotype, while the weight resting on and depressing this surface reflects the population density of that phenotype. A population’s mean phenotype will still evolve uphill toward the highest carrying capacity (Rosenzweig 1978; Abrams et al. 1993), but the increasing weight of numbers depresses this fitness peak as competition intensifies. If all phenotypes compete equally with each other (pure density dependence), the entire fitness surface is depressed evenly in proportion to total population density, while the location and relative height of the fitness peak remains the same. However, if competition is stronger between similar phenotypes (density and frequency dependence), then the weight of numbers only depresses the fitness surface locally. Such competition can disproportionately affect the most abundant (mean) phenotype even though it is adapted to the most abundant resource. Rarer consumer phenotypes may have fewer resources available, but also have fewer competitors with which to share those resources, so their overall fitness is relatively high. The population is thus subject to disruptive selection; that is, its mean phenotype is at or near a minimum on the fitness landscape (Dieckmann and Doebeli 1999). In the classical static model, a fitness minimum represents an unstable equilibrium. Although a population centered on 608 q 2004 The Society for the Study of Evolution. All rights reserved. 609 DISRUPTIVE SELECTION DUE TO COMPETITION this minimum will not show a directional phenotypic response, any perturbation to the phenotype distribution will lead to net directional selection away from the minimum. Disruptive selection should therefore be a rare and transient phenomenon. By contrast, disruptive selection can be stable when fitness is negatively frequency dependent. Theory suggests that populations will actually converge toward an optimum phenotype (determined by resource availability) that then becomes a fitness minimum (Dieckmann and Doebeli 1999). The population mean remains stuck at this minimum because perturbations to the phenotype distribution alter the shape of the fitness function driving the population back to the minimum, imparting stability (Abrams et al. 1993). This stability implies that disruptive selection could in fact be fairly common (Kingsolver et al. 2001). Stable fitness minima form the basis for a number of models of evolutionary diversification, including niche expansion (Roughgarden 1972), character displacement (Slatkin 1980), ecological sexual dimorphisms (Slatkin 1984), and sympatric speciation (Rosenzweig 1978; Dieckmann and Doebeli 1999; Doebeli and Dieckmann 2000). Despite its significant theoretical utility, there is little empirical support for the idea that intraspecific competition generates disruptive selection. Indeed one major proponent has recently written that ‘‘at present, this mechanism for fitness-minimizing equilibria is only a theoretical possibility, but a wide variety of ecological circumstances should lead to fitness functions with the necessary type of frequency-dependence. . . [including] a number of models of competition’’ (Abrams 2001, p. 278). One testable prediction of this body of theory is that populations experiencing higher competition should show faster niche expansion or stronger diversifying selection. Laboratory experiments using bacterial cultures (Helling et al. 1987; Rainey and Travisano 1998; Travisano and Rainey 2000; Buckling and Rainey 2002) and populations of fruit flies, Drosophila melanogaster (Bolnick 2001) have confirmed that competition can favor niche expansion. This paper adds to this literature by experimentally testing whether intraspecific competition can generate disruptive selection in natural populations of the three-spine stickleback, Gasterosteus aculeatus. Previous experimental studies of sticklebacks have shown that elevated competition strengthens directional selection for character displacement (Schluter 1994, 2003), and that phenotypically intermediate fish may experience reduced fitness due to resource competition (Hatfield and Schluter 1999; Vamosi et al. 2000). However, these studies used laboratory-reared populations with nonnatural phenotype distributions, generated by hybridizing already-diverged benthic and limnetic species pairs, and they did not directly test for disruptive selection. In this paper I describe an observational survey showing that, in natural populations, phenotypically intermediate sticklebacks are, on average, smaller and have lower relative gonad mass than phenotypically extreme individuals. Given that size and relative gonad mass are good predictors of fitness, these results suggest that natural populations are subject to disruptive selection on trophic morphology. By experimentally manipulating population density, I show that this disruptive selection depends on the level of competition. MATERIALS AND METHODS Study System Three-spine sticklebacks, G. aculeatus, are a widely distributed north temperate fish, whose marine populations repeatedly invaded freshwater habitats (Wootton 1984) and sometimes diversified into phenotypes using distinct microhabitats and eating different prey (Lavin and McPhail 1985). This diversification is most pronounced in a handful of lakes in British Columbia, where multiple invasions established benthic and limnetic species pairs (Taylor and McPhail 2000). However, the majority of populations in coastal British Columbia are composed of only a single species per lake. These solitary populations offer an ideal setting to test the theory of competitive disruptive selection because they fulfill two important assumptions underlying the theory. The first assumption is that competition is frequency dependent. Although stickleback populations have very catholic diets (Allen and Wootton 1984), individuals tend to specialize on subsets of the resources used by the population as a whole (Reimchen 1982; Reimchen and Nosil 2001a, b). This withinpopulation niche partitioning can occur between sexes (Reimchen and Nosil 2001b), or different phenotypes (Cresko and Baker 1996; Robinson 2000) and parallels the phenotypehabitat associations in two-species lakes. Individuals caught in open water tend to have longer gill rakers and smaller gape widths than individuals caught in the littoral zone (Schluter and McPhail 1992), reflecting strong functional trade-offs between using benthic and limnetic resources (Schluter 1995; Robinson 2000). This morphological variation has repeatedly been shown to have a significant heritable component (Day et al. 1994; Hatfield 1997). Because phenotypically divergent individuals are known to use different resources, the level of competition experienced by any given individual depends on the frequencies of similar and dissimilar phenotypes in its population (Schluter 2003). A second assumption is that competition is strong enough to drive natural selection. In the laboratory, sticklebacks show 20-fold variation in egg production depending on food supply (Wootton 1985), while male breeding activity and color depend on energy reserves (Stanley and Wootton 1986; Frischknecht 1993). Field experiments have shown that both growth and survival rates are depressed by competition, particularly when competition occurs between very similar phenotypes (Schluter 1994, 1995, 2003; Hatfield and Schluter 1999; Rundle et al. 2000; Vamosi et al. 2000; Pritchard and Schluter 2001). Finally, demographic studies of sticklebacks provide time-series data showing cyclical population fluctuations consistent with density-dependent population regulation (Wootton and Smith 2000). Given that sticklebacks fulfill these two prerequisites for competitive disruptive selection, I first predicted that trophic morphology may naturally be subject to disruptive selection in solitary populations. I tested this hypothesis in two lakes in the Amor de Cosmos River watershed in northern Vancouver Island, British Columbia (Table 1). Next, I experimentally manipulated population density in five lakes in this watershed to test whether the observed disruptive selection was driven by competition (Fig. 1). 610 DANIEL I. BOLNICK TABLE 1. Information on the six lakes used in this study, including longitude and latitude, the year in which observational and experimental studies were conducted in a given lake, the number of fish transferred out of low-density enclosures (LD) and into highdensity enclosures (HD), and sample sizes of fish captured from each enclosure at the end of the five-week experiments. All lakes are part of the Amor de Cosmos watershed of Vancouver Island, British Columbia. Lake Coordinates Cecil Lake Cedar Lake Dugout Lake1 Farewell Lake Little Mud Lake Muskeg Lake 508149200N, 508129340N, 508109510N, 508119580N, 508129240N, 508119580N, 1258329310W 125834930W 1258319310W 125835990W 125832900W 1258349380W Test for disruptive performance 1999 2001 Density experiment No. fish removed from LD No. fish added to HD 20022 56 76 126 74 240 223 409 401 337 267 420 469 2002 2002 20023 2001 20023 No. fish recaptured LD HD 142 97 182 47 49 50 202 180 119 65 150 50 1 No official name available. 2 Experiment not feasible due to dense submerged logs and branches. 3 Experiment failed due to insufficient recapture rates. Testing for Disruptive Selection To test for disruptive selection, one must measure the morphology and fitness of a large sample of individuals and then determine whether fitness is a quadratic function of morphology. Unfortunately, sticklebacks are small fish that exist at high population densities, precluding techniques such as mark-recapture that are necessary to directly estimate individual survival or fecundity. Also, key aspects of trophic morphology can only be measured invasively. Consequently, I did not directly estimate fitness, but instead measured two performance variables. Both body size and relative gonad mass are known to be correlated with energy income and potential fecundity, and so they are useful proxies for fitness (Wootton 1976, 1994; Bell and Foster 1994). Total fecundity in females can be divided into several components: clutch size, spawning frequency, and egg quality (mass, nutrient content). Prebreeding food supplies determine an individual’s growth rate and hence size at initial spawning, the primary determinant of clutch size (Wootton 1973a, b; Fletcher and Wootton 1995). Spawning frequency is also an important component of fecundity, as females can range from zero to 10 spawnings per season in the field depending on their energy income during breeding (r2 5 0.829, Ali and Wootton 1999; see also Wootton 1977). In turn, high spawning frequency is reflected in higher average gonad mass through time. In males, energy income is also used for growth (favored by sexual selection) and to maintain spermatogenesis (Huntingford et al. 2001). Although overall male gonad mass is quite low, body energy reserves are significantly depleted to build and maintain testes mass, and energy-limited males have reduced testes mass and function (Huntingford et al. 2001). Hence, both body size and relative gonad mass are known to respond to foraging success and competition and to predict reproductive potential. I captured sticklebacks from marsh and open-water areas of Cedar Lake (1999, N 5 171) and Muskeg Lake (2001, N 5 150), using dipnets and minnow traps. All fish were euthanized in MS-222, following University of California at Davis Animal Use and Care protocol no. 9334. Specimens were immediately placed in liquid nitrogen for transport back to Davis, where they were stored at 2808C until needed for analysis. I sexed and weighed each fish and measured (to 0.01 mm) the standard length, head length, snout length, eye width, interorbital width, interopercular width, head depth, body depth, upper jaw length, and (open) gape width on each individual. All measurements followed Lavin and McPhail (1985), except for gape width (which they measured on the closed mouth) and interopercular width, the maximum width between the right and left opercula when the mouth is closed. I then counted the number of gill rakers on the first right branchial arch. I used an ocular micrometer to measure the lengths of the three longest gill rakers. Gonads were weighed to 0.0001 g immediately (,5 sec) after removal. This precision is reliable within the first 8–10 sec following removal, FIG. 1. Three hypotheses as to how disruptive fitness functions might respond to experimental manipulation of population density. (A) If fitness is density independent, both high- and low-density populations (HD and LD) will have similar fitness functions. (B) If fitness is density dependent, HD should result in lower fitness, but all phenotypes are affected equally so the slope will not change. (C) If fitness is density and frequency dependent, disruptive selection will be reduced in LD and exaggerated in HD. DISRUPTIVE SELECTION DUE TO COMPETITION after which desiccation introduces significant measurement error (D. I. Bolnick, unpubl. data). I tested for disruptive performance functions (a proxy for disruptive selection) by relating body size or relative gonad mass to size-independent axes of trophic morphology. To isolate orthogonal axes of morphological variation for each lake, I ran a principal components analysis (PCA) on the correlation matrix of the log-transformed morphometric data and retained individuals’ factor scores for the first three principal component axes (PC1, PC2, and PC3). Body size was measured as the first principal component axis (PC1). To quantify relative gonad mass, I used individuals’ residuals from the regression of log-transformed gonad mass on log body mass, sex, and a mass 3 sex interaction. Fish infected with the cestode Schistocephalus solidus (which fill the body cavity and can weigh over 25% of the fish’s body mass) have severely atrophied gonads (Heins and Baker 2003) and were excluded from this analysis. All statistical analyses were performed using Systat 9.0 (Systat Inc., Evanston, IL). Quadratic regression of each performance variable on morphology indicates disruptive performance when the slope of the quadratic term (g) is significantly positive (Lande and Arnold 1983). Using body size as the fitness proxy, PC1 was regressed on PC2, PC22, PC3, and PC32. Gonad mass residuals were regressed on PC1, PC12, PC2, PC22, PC3, and PC32. The PC1 terms were included as independent variables in the gonad mass regression to check whether gonad residuals were independent of body size (confirmed in all tests). I used a partial F-test to determine whether any significant quadratic term significantly improved the fit of the model. The data fit the assumptions of the GLM (normally distributed variables and homoscedastic residuals). Quadratic regression has two important weaknesses. First, even monotonic functions can yield significant quadratic terms if they are sufficiently concave or convex, even if there is no minimum or maximum within the range of the data (Mitchell-Olds and Shaw 1987). Second, quadratic regression is very sensitive to outliers and can yield false positives. Nonparametric cubic spline circumvents both flaws and allows estimation of a fitness function without an a priori assumption about its shape (Schluter 1988). I used cubic spline to visualize the fitness functions to look for a minimum within the range of the data, with 1000 bootstraps of the data to estimate 95% confidence intervals around this curve (program from D. Schluter). Experimental Test of the Role of Competition I experimentally manipulated population density to test whether disruptive selection was stronger in populations experiencing higher competition (Fig. 1). The experiment was carried out in Muskeg Lake in 2001 and in five lakes in 2002 (Table 1). In each lake, I built a pair of large enclosures by placing two semicircular barriers against the lakeshore, thereby enclosing both open water, marsh, and shoreline habitat. The barriers were made of panels of 1/16-in seine net (in 2001) or 4 mm SuperDura greenhouse plastic (in 2002; AT Plastics Inc, Brompton, Ontario, Canada), 33 m long and 2– 5 m wide. Panels were secured to the lake bottom by lead line, rocks, stakes, and metal chain, while the top of the panel 611 was held above the surface of the water by closely spaced fishing net floats (2001) or styrofoam tubes (2002). The ends of the panels were attached to 1-m high 1/16-in plastic fencing buried 10 cm into the substrate, which extended the enclosures through shallow water, marsh, and up onto dry land. Each enclosure contained at least 150 m2 and as much as 250 m2 of lake surface, including marsh, channels, and open water up to 2 m (Muskeg, Dugout Lakes) or 4 m (Cecil, Farewell, Mud Lakes) deep. Scuba divers checked to ensure that the bottoms of all enclosures were sealed to the substrate. Within each lake, I used minnow traps and dipnets to remove fish from one enclosure to generate a low-density treatment (LD) and added those fish to the second enclosure to yield a high-density treatment (HD). To further elevate density in HD, I added additional fish caught from the unenclosed lake. My intent was to reduce the LD enclosure to approximately half its normal density and to double the density in HD. The upper target was chosen based on densities used in the many experimental pond studies of competition by Schluter and colleagues (e.g., Schluter 1994, 2003). The advantage of this approach was that it allowed me to use a natural phenotype distribution drawn from the resident population within each lake. Natural populations are more likely to have converged to a stable fitness minimum than fish introduced from a laboratory breeding program. The mean phenotype in natural populations appears to track the relative availability of benthic and limnetic prey items (Lavin and McPhail 1986). The disadvantage of using the native stickleback population was that density manipulations were necessarily inexact because the population densities in each enclosure could not be known precisely. I estimated population densities in the LD enclosure and in an unenclosed area of each lake, using Zippin’s maximum-likelihood removal method (Zippin 1956, 1958; Southwood and Henderson 2000). Capture rates decline over time as individuals are removed from an area. Assuming a constant capture effort and constant capture probability per individual, it is possible to estimate the original density based on the time series of how capture effort declines. For example, in Muskeg Lake in 2001 I estimated that the LD enclosure contained 480 fish. Consequently, I removed 240 fish from LD, and added 420 to HD (the 240 from LD plus as close to 240 as I could capture in the available time from outside the enclosures). Because capture probability is not likely to be constant, I treated these estimates only as a rough guide. In Mud and Dugout Lakes, fish densities in LD were unusually low even before trapping, presumably due to disturbance while building the enclosures. Equivalent habitat just outside the enclosures yielded five times higher capture rates. Consequently, I removed few fish from LD in those lakes, but still added a high number of fish to HD from outside the enclosures to ensure high density (Table 1). In early June, five weeks after density manipulation, I captured all surviving fish (but not more than 200) from LD and HD (Table 1), using dipnets, minnow traps, and a seine net. Mud and Muskeg Lakes had very low capture rates (Table 1) and were excluded from subsequent analyses because sample sizes were too low to offer any reasonable power to accurately estimate quadratic slopes. The decision to omit these lakes was made prior to data collection or analysis. In Fare- 612 0.04 0.04 0.03 0.03 0.05 0.06 0.09 0.03 0.06 0.02 0.03 0.96 20.04 20.04 20.05 7.22 PC3 PC2 0.20 0.21 0.14 0.08 0.18 0.89 0.10 0.19 0.18 0.12 0.18 20.16 20.73 20.75 20.79 15.37 0.97 0.96 0.98 0.97 0.92 0.92 0.94 0.96 0.96 0.97 0.88 20.23 0.67 0.65 0.60 72.75 0.08 0.09 0.08 0.08 0.08 0.07 0.09 0.07 0.07 0.06 0.07 0.76 20.27 20.27 20.28 5.81 0.13 0.12 0.08 0.08 0.11 0.06 0.13 0.12 0.13 0.06 0.08 20.62 20.45 20.48 20.47 7.86 0.98 0.98 0.99 0.98 0.97 0.97 0.98 0.99 0.98 0.98 0.98 20.18 0.84 0.83 0.81 84.35 0.04 0.03 0.02 20.02 0.05 0.01 0.04 0.02 0.03 0.00 0.02 20.95 20.14 20.15 20.18 4.37 0.14 0.13 0.10 0.07 0.11 0.08 0.12 0.10 0.12 0.07 0.11 0.23 20.36 20.40 20.44 6.54 0.98 0.99 0.99 0.98 0.97 0.94 0.98 0.99 0.98 0.98 0.98 20.23 0.91 0.90 0.87 86.51 0.00 0.03 0.02 0.03 0.02 0.00 0.02 0.02 0.00 0.02 0.04 0.99 20.08 20.07 20.06 6.60 0.17 0.17 0.13 0.12 0.17 0.08 0.16 0.14 0.15 0.08 0.12 20.17 20.63 20.66 20.70 10.36 0.98 0.97 0.99 0.98 0.95 0.94 0.98 0.98 0.97 0.97 0.98 20.04 0.76 0.74 0.69 79.70 0.01 0.01 0.02 0.04 0.01 20.07 0.01 0.01 0.00 0.05 0.06 20.99 0.08 20.05 20.05 5.93 0.15 0.15 0.10 0.04 0.10 0.02 0.24 0.17 0.16 0.08 0.11 0.12 20.75 20.76 20.77 11.75 0.98 0.98 0.98 0.96 0.91 0.88 0.95 0.96 0.96 0.95 0.92 20.02 0.65 0.64 0.62 74.67 Body mass Standard length Head length Snout length Eye width Interorbital width Interopercular width Head depth Body depth Upper jaw length Gape width Gill raker number Gill raker length (1) Gill raker length (2) Gill raker length (3) Percentage variance Muskeg Lake PC1 PC3 PC2 Farewell Lake PC1 PC3 PC2 Dugout Lake PC1 PC3 PC2 Cecil Lake PC1 PC3 PC2 Principal component analysis identified three major axes of morphological variation in each lake (axes that explain . 5% of the variation; Table 2). PC1 can be interpreted as a measure of body size, because linear morphometric measurements show strong even loadings on this axis. PC2 and PC3 load very heavily on gill raker length and gill raker number respectively (Table 2). Fitness proxy estimates of the fitness function suggest that sticklebacks in Cedar Lake were subject to disruptive selection on size-adjusted gill raker length. Both body size (PC1) and relative gonad mass had significant positive quadratic regression terms with respect to gill raker length (PC2; Table 3). In both cases, partial F-tests confirmed that including PC22 in the multiple regression significantly improved the fit Cedar Lake Disruptive Performance Functions PC1 RESULTS Trait well Lake, more fish were recovered from LD than from HD. This could reflect high mortality in HD, unnoticed damage to the HD enclosure that let fish escape, or damage to the LD enclosure that let fish enter. In the following analyses, the Farewell HD enclosure was nevertheless treated as the high-competition population. This judgment is supported by zooplankton sampling showing lower zooplankton densities in HD than LD (D. I. Bolnick, unpubl. data), and because HD fish were significantly smaller than LD fish at the end of the experiment (see Results). As described above, specimens were euthanized in MS222, frozen in liquid nitrogen, returned to Davis, California, then weighed, measured, and sexed. I again used PCA to estimate individuals’ body size (PC1) and two size-independent measures of trophic morphology (PC2, PC3), and regression residuals to calculate relative gonad mass. Both PCA and the gonad mass regression were carried out, pooling all individuals (HD and LD) caught in a given lake. To test for disruptive selection within each experimental enclosure, I ran quadratic regressions of body size (PC1) and relative gonad mass as functions of gill raker length (PC2) and the square of gill raker length (PC22). The estimated coefficient of the quadratic term, g, indicates the strength and direction of the quadratic selection for each treatment in each lake. Statistically significant quadratic terms were double-checked by cubic spline analysis. To test whether disruptive selection is stronger in HD than LD within a given lake, I used a general linear model with each performance variable dependent on treatment, PC2, PC22, PC2 3 density, and PC22 3 density. A significant quadratic 3 treatment interaction term indicates that quadratic selection is different between competition treatments within the lake, and the direction of this difference is found by comparing the estimates of the quadratic slopes, g. Note that the initial hypothesis is directional (HD . LD), so onetailed tests are appropriate and the P-values for the PC22 3 density interaction terms are adjusted accordingly. To analyze the results across all replicate lakes together, I ran a paired t-test comparing the g estimates from HD and LD, paired by lake. This tests the one-tailed hypothesis that disruptive selection was consistently larger in HD than LD (Fig. 1C). TABLE 2. Loadings of morphological variables on the first three principal component axes (PC1, PC2, and PC3), and the percent variance explained by each axis, divided up by lake. Mud Lake and the 2002 experiment in Muskeg Lake are not included because too few fish were recaptured to warrant measurement and analysis. DANIEL I. BOLNICK 613 DISRUPTIVE SELECTION DUE TO COMPETITION TABLE 3. Tests for disruptive performance functions in two natural populations. Two performance variables serve as proxies for fitness: body size variation (PC1) and relative gonad mass. Regression terms are listed for each fitness proxy within each lake, together with the estimated coefficient for each term, its standard error (SE), t-statistic, and probability of the null hypothesis that the estimated coefficient is zero. Positive coefficients represent disruptive selection, negative coefficients are stabilizing. Bold rows highlight the statistically significant regression terms. Lake, year Cedar Lake, 1999 Performance variable body size (PC1) relative gonad mass Muskeg Lake, 2001 body size (PC1) relative gonad mass Regression term Coefficient SE t P PC2 PC22 PC3 PC32 PC1 PC12 PC2 PC22 PC3 PC32 PC2 PC22 PC3 PC32 PC1 PC12 PC2 PC22 PC3 PC32 20.061 0.284 0.023 20.086 0.019 20.019 20.115 0.139 0.047 20.071 20.032 0.031 0.002 0.125 0.008 20.0176 0.004 20.078 20.083 0.027 0.073 0.067 0.072 0.061 0.079 0.058 0.058 0.06 0.09 0.071 0.095 0.046 0.085 0.062 0.066 0.046 0.072 0.035 0.067 0.047 20.834 4.246 0.32 21.396 0.238 20.332 21.923 2.382 0.522 21.001 20.339 0.659 0.022 2.03 0.127 20.381 0.055 22.238 21.236 0.566 0.405 ,0.001 0.749 0.164 0.813 0.741 0.058 0.02 0.603 0.32 0.735 0.511 0.983 0.044 0.899 0.704 0.956 0.027 0.219 0.572 of the model (PC1: F1,168 5 18.0, P , 0.001; relative gonad mass: F1,168 5 4.53, P 5 0.036). Cubic spline analysis confirmed that there was a performance minimum. Individuals with intermediate gill raker lengths (PC2) had lower mean body size (Fig. 2A) and relative gonad mass (Fig. 2B) than individuals with long or short gill rakers. In contrast, body size variation in Muskeg Lake showed no relationship with PC2 (gill raker length). Gill raker number (PC3) did have a significant quadratic term (Table 3), but did not significantly improve the fit of the regression model (partial F-test: F1,133 5 3.62, P 5 0.059). In contrast, relative gonad mass showed a weakly stabilizing performance function with respect to gill raker length (Table 3), supported by cubic spline analysis and a partial F-test (F1,133 5 5.08, P 5 0.026). Effect of Competition Experimental manipulation of population density had a weak but significant effect on the quadratic slope of the performance function, matching the prediction derived from the theory of competitive disruptive selection (Fig. 1C). This effect is seen most clearly in the 2001 Muskeg Lake experiment (Fig. 3). Gill raker length (PC2) is subject to disruptive selection in HD but not in LD (Table 4), using either PC1 or relative gonad mass as a fitness proxy. A general linear model analyzing Muskeg Lake’s HD and LD together supports two conclusions. First, fish from the HD enclosure were significantly smaller (density effect: F1,193 5 11.264, P 5 0.001) and had less gonad mass given their size (density effect: F1,193 5 14.066, P , 0.001) than LD fish. This suggests that density manipulations had the expected effect on performance variables, underscoring their utility as measures of the detrimental effects competition. Quantitative zooplankton samples with a Wisconsin zoo- plankton net independently confirmed that the HD enclosure had significantly lower zooplankton density (D. I. Bolnick, unpubl. data). Second, there was a significant quadratic 3 experimental treatment interaction term, indicating that HD fish experienced significantly stronger disruptive performance than LD fish (PC1: F1,193 5 3.355, P 5 0.035; relative gonad mass: F1,193 5 5.184, P 5 0.012; Fig. 3). Replicating this experiment across five lakes in 2002, the results within individual lakes are less compelling than the 2001 experiment. As noted above, Mud and Muskeg Lakes were not analyzed because of low recapture rates. Analyzing the three remaining lakes (Cecil, Dugout, and Farewell) yielded variable results. Density manipulations significantly reduced body size in HD relative to LD in two of the three lakes (Cecil and Farewell; Table 5), indicating that competition had effectively reduced growth rates. Using body size as the fitness proxy, gill raker length was subject to significant disruptive selection in HD enclosures in two of the three lakes (Dugout and Farewell; Table 5). There was a significant treatment 3 PC22 interaction effect only within Dugout Lake, in which disruptive performance was stronger in HD than LD (F1,249 5 4.7, P 5 0.031). However, relative gonad mass showed no significant effect of competition, no significant disruptive selection in HD, and no treatment 3 PC22 interaction in any of the three lakes (Table 5). The nonsignificant results must be treated with caution, as the sample sizes from any given enclosure are low enough to limit statistical power to detect quadratic regression terms. It is generally recommended that tests for disruptive selection use sample sizes of 500–1000 individuals (Kingsolver et al. 2001). Unfortunately, the sample sizes in this study were limited by enclosure size and survivorship within each enclosure. Although the 2002 experiments only revealed an interaction between competition treatment and a quadratic perfor- 614 DANIEL I. BOLNICK FIG. 2. Cubic spline estimates of fitness functions for gill raker length (PCA-2), in the Cedar Lake population. Two performance variables serve as proxies for fitness: (A) body size variation (PCA1) and (B) relative gonad mass. Cubic splines (thicker center line) are bracketed by their 95% confidence intervals estimated from 1000 bootstrap replicates. mance slope within one lake, analyzing all four experimental lakes together (including Muskeg Lake from 2001) yields a more consistent picture. Pairing quadratic slopes, g, from the two enclosures within each lake, a one-tailed paired t-test confirmed that g was consistently larger in HD than LD using either performance variable (body size: t3 5 2.383, P 5 0.048; Fig. 4A; relative gonad mass: t3 5 2.49, P 5 0.044; Fig. 4B). Hence, while disruptive performance was not always statistically significant within HD enclosures, and only half the lakes showed a significant interaction between competition and the quadratic term, the direction of the effect is consistent across lakes. This supports the original hypothesis that disruptive selection is stronger in environments with higher competition. This conclusion is further illuminated by considering the among-lake variation in the effect of competition on g. While this variation may well be a result of idiosyncratic variation FIG. 3. Quadratic regression estimates of gill raker length fitness functions in high- and low-density treatments (HD and LD) in Muskeg Lake, 2001. The quadratic regression term is significant in HD (V) but not LD (3) for both fitness proxies. Fitness proxies are; (A) body size (PC1) and (B) relative gonad mass. among the lakes, it may also reflect differential success in manipulating population density. To test this possibility, I used the ratio of the number of recaptured fish in HD and LD (Table 1) as a very rough measure of the efficacy of the density treatment. The contrast between HD and LD quadratic slopes (gHD 2 gLD) is positively correlated with this density ratio (body size: r 5 0.794, P 5 0.206; relative gonad mass; r 5 0.798, P 5 0.202). While these correlations are not statistically significant (perhaps due to very low power), they are at least worth mentioning because the correlation coefficients are large and in a direction consistent with competitive disruptive selection. DISCUSSION Intraspecific competition has long been thought to drive niche expansion and favor increased trophic variation within a population (Darwin 1859; Mayr 1942, 1963; Ludwig 1950). 615 DISRUPTIVE SELECTION DUE TO COMPETITION TABLE 4. Tests of disruptive selection on gill raker length (PC2) within each density treatment (HD or LD) in each lake. Body size (PC1) and relative gonad mass provide independent estimates of fitness. The quadratic regression coefficient (g), its standard error (SE), and its statistical significance (P) are provided for every fitness function. Within each lake a general linear model (GLM) tested for an effect of density manipulation (density), and for a density by quadratic interaction term (density 3 PC22). Bold terms indicate statistically significant effects. Note that because the experiment was testing a one-tailed hypothesis (disruptive selection is stronger in high density), the P-vales for the density 3 PC22 interaction terms are adjusted to reflect the one-tailed test. GLM P-values Quadratic regression term Fitness measure Relative body size Lake Cecil Dugout Farewell Muskeg1 Relative gonad mass Cecil Dugout Farewell Muskeg1 1 Treatment g SE P HD LD HD LD HD LD HD LD HD LD HD LD HD LD HD LD 0.052 0.019 0.177 0.018 0.11 0.094 0.203 0.06 20.002 20.009 0.03 20.07 0.04 20.017 0.124 20.037 0.042 0.073 0.057 0.069 0.047 0.06 0.053 0.057 0.04 0.054 0.052 0.063 0.049 0.049 0.045 0.056 0.232 0.766 0.002 0.796 0.021 0.119 0.0001 0.3 0.96 0.963 0.95 0.276 0.425 0.73 0.01 0.67 Density Density 3 PC22 0.034 0.337 0.65 0.031 0.005 0.44 0.001 0.035 0.96 0.46 0.351 0.19 0.833 0.249 ,.001 0.012 A 2001 experiment. Ludwig (1950) referred to this competitive niche diversification as ‘‘annidation.’’ While this particular term never gained wide usage, the basic process has continued to play an important role in a number of evolutionary-ecology models (Schluter 2000). For example, verbal (Rosenzweig 1978; Gibbons 1979), analytical (Slatkin 1984; Doebeli 1996; Drossel and McKane 2000), and simulation models (Dieckmann and Doebeli 1999; Bolnick and Doebeli 2003) have all suggested that competition can generate disruptive selection. In turn, this selection may serve as the driving force for niche expansion (Roughgarden 1972), sexual dimorphism (Slatkin 1984), or speciation (Doebeli 1996; Dieckmann and Doebeli 1999). Despite the substantial theoretical efforts built on this foundation, there have been few if any direct empirical tests—observational or experimental—of whether intraspecific competition causes disruptive selection. This paper describes one such empirical test, using phenotypically intermediate populations of the three-spine stickleback as a study system. Sticklebacks show substantial within-population niche variation (Schluter and McPhail 1992; Schluter 1993, 1995; Cresko and Baker 1996; Robinson 2000; Vamosi et al. 2000; Reimchen and Nosil 2001a, b; D. I. Bolnick, unpubl. data), and hence are likely to experience frequency-dependent competition, which can in turn produce stable fitness minima (disruptive selection). In a survey of two natural populations, I found evidence that trophic morphology (gill raker length) was under disruptive selection in one lake. Two independent proxies for fitness both indicated that phenotypically intermediate fish fared worse than fish with large or small gill rakers. In contrast, trophic morphology did not appear to be subject to disruptive selection in Muskeg Lake. The fact that Muskeg Lake gave the strongest experimental result indicates that there is nothing intrinsic to the lake or its populations that would prevent natural disruptive selection. This dis- crepancy may reflect year-to-year variation in the level of competition, either due to fluctuations in resource density or stickleback population density. Natural stickleback populations are known to fluctuate cyclically, suggesting that the intensity of intraspecific competition experienced by any population may be quite variable through time (Wootton and Smith 2000). Population densities in Muskeg Lake appeared to be experiencing a short-term decline, as capture rates (in different parts of the lake) fell between my first visit in 2000 and the 2001 survey reported here and were even lower in 2002 (pers. obs.). While the results from Cedar Lake were consistent with predictions derived from theory, such observational approaches cannot directly identify the ecological mechanism causing the selection. For example, Robinson and Wilson (1996) showed that phenotypically intermediate pumpkinseed sunfish (Lepomis gibbosus) were smaller and had lower stored lipid levels, but did not establish the causal mechanism behind this pattern. They argued that their results were evidence for functional trade-offs, in which intermediate fish were ‘‘jacks of all trades but masters of none’’ (Fig. 1A, B), but did not test the alternative hypothesis of competitive disruptive selection (Fig. 1C). The experimental manipulation of population densities reported in this paper allows me to reject both the densityindependent and purely density-dependent explanations (Fig. 1 A, B) of the quadratic function observed in the unmanipulated population in Cedar Lake. The quadratic slope of both fitness proxies were consistently if only slightly steeper in high-density than in low-density populations. This strongly implies that intraspecific competition can generate disruptive selection and hence could be responsible for the inferred disruptive selection in the unmanipulated Cedar Lake population. It is worth noting that the slopes of experimentally 616 DANIEL I. BOLNICK FIG. 4. Effect of competition (high- and low-density treatments, HD and LD) on the quadratic slope of the gill raker length fitness function (g). Two performance variables serve as proxies for fitness: (A) relative body size (PC-1) and (B) relative gonad mass. Lines connect the quadratic slopes from HD and LD enclosures paired within a given lake (M, Muskeg Lake 2001; D, Dugout Lake; F, Farewell Lake; C, Cecil Lake). Points above the thin horizontal line have a positive (disruptive) slope. Asterisks indicate the statistical significance (*P , 0.05; **P , 0.01; ***P , 0.001) of quadratic slopes. Asterisks next to the lines connecting enclosures indicate the significance of the density 3 PC22 interaction within the lake. induced disruptive selection in high-density treatments were similar to the quadratic slope observed in Cedar Lake. Although quadratic slopes were statistically significant, there was substantial scatter around the regression lines, and the function slopes were shallow. The estimated quadratic slopes (g) ranged from 0.05 to 0.2 (body size) and 20.002 to 0.124 (relative gonad mass) in the high-density treatments. This raises the obvious concern that the observed disruptive selection may be statistically but not biologically significant, too weak to drive any evolutionary response. Several observations suggest that this concern is unwarranted. First, the magnitude of disruptive selection documented here is similar to that observed in other studies of disruptive selection. The median slope of quadratic fitness functions in natural populations is only 0.10 (Kingsolver et al. 2001), although it is worth noting that their review did not distinguish between curved monotonic slopes and true disruptive selection that has a minimum. Second, even very weak selection gradients can have substantial evolutionary consequences over the long term. Population genetic models generally assume selection strengths that are orders of magnitude weaker than what we can observe empirically, yet still find that selection can be effective in changing gene frequencies and phenotype distributions (in particular, changing the variances, because selection is quadratic here). Theoretical models of sympatric speciation suggest that the condition for evolutionary branching is the presence or absence of disruptive selection and not its strength (Dieckmann and Doebeli 1999). Although the results documented in this paper demonstrate that frequency-dependent competition can generate disruptive selection, whether it commonly does so in undisturbed populations is an open question. The answer will depend on both the selective importance of intraspecific competition in natural populations and on the degree of individual specialization needed to generate frequency dependence. In testing the theory of competitive disruptive selection, I consciously selected a study system that satisfied both of these conditions. A survey of gut contents in Cedar Lake sticklebacks found that over 60% of the resource breadth in that population could be attributed to between-individual variation: using Roughgarden’s Shannon-Weaver index of intrapopulation variation (Roughgarden 1974, 1979; Bolnick et al. 2002), total niche width 5 1.63; within-individual component 5 0.61; betweenindividual component 5 1.02, so WIC/TNW 5 0.37 (D. I. Bolnick, unpubl. data). If this variability is highly unusual, then the dynamics described in this paper may be quite rare. Currently, it is difficult to address this question, as very few studies have quantified the degree of individual specialization in a comparable manner. However, there are many published examples of individual-level niche variation, found across a broad array of taxa (Bolnick et al. 2003). Furthermore, quadratic fitness and performance function slopes found in other studies (Robinson and Wilson 1996; McLaughlin et al. 1999; Kingsolver et al. 2001) suggest that disruptive selection may be more common than generally appreciated. Even if competitive disruptive selection proves to be common, its evolutionary consequences are not straightforward. Random mating, phenotypic plasticity, balancing effects of other selective forces such as predation or sexual selection, or fluctuations in the level of competition could all mitigate the long-term effect of this selection. It is unclear how these factors affect the likelihood of evolutionary processes such as adaptive speciation that are thought to rely on competitive disruptive selection (Rosenzweig 1978; Udovic 1980; Dieckmann and Doebeli 1999; Kondrashov and Kondrashov 1999; Drossel and McKane 2000). Furthermore, there are multiple alternative evolutionary responses to disruptive selection. For example, theory suggests that both speciation and sexual dimorphisms are possible responses to disruptive selection (Bolnick and Doebeli 2003). Which one occurs will depend on the genetic covariance between male and female traits and the genetic potential for assortative mating (Bolnick and Doebeli 2003). Polymorphisms or simply increased phenotypic variance are also reasonable outcomes. Consequently, we cannot yet make any statements about the generality of competitive disruptive selection or its evolutionary consequences. What is clear is that competition does have the potential to drive evolutionary diversification in natural populations. ACKNOWLEDGMENTS I thank P. Abrams, R. Calsbeek, P. Nosil, T. Schoener, T. Smith, and P. Wainwright for their comments on this man- DISRUPTIVE SELECTION DUE TO COMPETITION uscript. J. Boughman, D. McPhail, H. Rundle, D. Schluter, S. Vamosi, and P. Wainwright provided helpful advice and criticism. D. A. Bolnick, D. J. Bolnick, C. Buck, B. Spitzer, and K. van der Laan helped set up the field experiments. L. Carswell at the Ministry of Environment, Lands and Parks arranged permits for field work. This research was supported by a National Science Foundation (NSF) Graduate Research Fellowship, an NSF Dissertation Improvement Grant (DEB0105147) to DIB and P. 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