| HOME | HELP | FEEDBACK | SUBSCRIPTIONS | ARCHIVE | SEARCH | TABLE OF CONTENTS |
Department of Biology II, Section of Evolutionary Biology, University of Munich, 82152 Planegg-Martinsried, Germany
2 Corresponding author: Department of Biology II, University of Munich, Grosshaderner Str. 2, 82152 Planegg-Martinsried, Germany.
E-mail: stephan{at}zi.biologie.uni-muenchen.de
 |
ABSTRACT |
|---|
 TOP ABSTRACT MATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
10,000–15,000 years ago (DAVID and CAPY 1988; LACHAISE et al. 1988). D. ananassae, another cosmopolitan species in the melanogaster group, is thought to have its origin in Southeast (SE) Asia (TOBARI 1993). A recent multilocus study of worldwide populations of D. ananassae substantiates this claim, defining the ancestral range of this species to be a region of SE Asia that existed as a single landmass (Sundaland) during the late Pleistocene (18,000 years ago), while other populations including those in more temperate regions appear to be more recent colonizations (DAS et al. 2004, accompanying article in this issue). Thus, a similar scenario is emerging for this species, with the invasion of new climatic zones providing a priori expectation that local populations have adapted to their new environments. However, in contrast to D. melanogaster, D. ananassae is a species displaying significant population structure, enabling the footprints of natural selection at the DNA level to be analyzed in a subdivided population. Previous studies of four D. ananassae populations (Nepal, Myanmar, India, and Sri Lanka) found compelling evidence for the action of natural selection at loci in regions of low recombination (STEPHAN et al. 1998; CHEN et al. 2000). At both the vermilion (v) and furrowed (fw) loci, a pattern of homogenization of allele frequencies within, but differentiation between geographic regions [i.e., North (Nepal, Myanmar) vs. South (India, Sri Lanka)] was found. In both studies, this homogenization of allele frequencies in the northern populations rejected a model of background selection against deleterious mutations (CHARLESWORTH et al. 1993), instead favoring a model of the spreading of a beneficial allele (the selective sweep model; MAYNARD SMITH and HAIGH 1974; KAPLAN et al. 1989; STEPHAN et al. 1992). At the fw locus, the background selection model was rejected for the southern populations as well (CHEN et al. 2000), raising several important questions about the mode of selective sweeps in this subdivided species. Namely, is this pattern best explained by a single sweep (SLATKIN and WIEHE 1998), or have two independent sweeps occurred? Furthermore, the geographic distribution of the sweep(s) is unknown, as is whether it is associated with adaptation to novel environments. Given that D. ananassae is highly structured and occupies a wide range of climatic zones, answers to these questions would also shed light on the role of natural selection in genetic differentiation.
For these reasons, we have expanded the study of nucleotide variation at the fw locus to include 13 populations, spanning a majority of the species range of D. ananassae. In contrast to previous studies, polymorphism data were collected by PCR and direct sequencing rather than by single-strand conformation polymorphism (SSCP) and stratified sequencing. The migration behavior of this selected locus is compared to that of 10 independent neutrally evolving loci (DAS et al. 2004), which alleviates the potential stochasticity of single-locus estimates of the migration rate. The pattern of differentiation between pairs of populations is tested against alternative models of selection by the FST test of background selection (STEPHAN et al. 1998; CHEN et al. 2000). To further understand the nature of the selective forces shaping variation at fw, the distribution of fw haplotypes is analyzed with respect to population latitude.
|
MATERIALS AND METHODS |
|---|
|
TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
|
400–500 bp apart. Sequencing was performed on a Megabace 1000 automated DNA sequencer (Amersham Biosciences, Buckinghamshire, UK). The primer sequences and cycling conditions for both PCR and sequencing reactions are available from the authors upon request.
|
, was estimated according to WATTERSON (1975) and 
according to NEI (1987).
Pairwise HKA tests:
The HKA test (HUDSON et al. 1987) was performed for all pairwise comparisons between loci [11 loci (fw + 10 neutral loci) 
55 comparisons], for each of the 13 sampled populations using a program kindly provided by Lino Ometto. For each population, the probability of observing at least i significant tests at the fw locus given that n paired tests were performed and k were significant between the l loci was calculated by
 | (1) |
FST test of the background selection model:
The original development of this test is described in STEPHAN et al. (1998) and was modified by CHEN et al. (2000). In summary, this test takes into account the effect of background selection and recombination on the effective population size of the locus of interest, enabling the effect of background selection on neutral variation in a subdivided population to be approximated by simulating the neutral coalescent under a model of population structure. In these simulations, the finite island model (CROW 1986, Chap. 3.4) is used. The per-locus nucleotide diversity 
S, the migration rate MS, and the recombination rate RS at the locus putatively under selection are specified along with the number of subpopulations, k.
The migration rate at the locus putatively under selection, MS, is estimated from the data
 | (2) |
S and 0 are the arithmetic means of the per-site nucleotide diversities in the two subpopulations at the locus putatively under selection and the average of 10 neutral loci, respectively. The factor fS0 takes differences in the neutral mutation rate between loci into account (CHEN et al. 2000).
Analysis of clinal variation:
To assess the association of allele frequency with population sample latitude, a linear regression analysis was performed. If selection affecting the observed distribution of fw haplotypes is attributable to an environmental gradient covarying with latitude, allele frequencies at fw may be expected to display a latitudinal cline. This analysis was performed on both a haplotype and a site-by-site basis following the design of BERRY and KREITMAN (1993). To distinguish between the effects of selection and population history, clinal variation at fw was compared to that observed at 10 neutrally evolving loci.
To assess the statistical significance of clinal variation, haplotype and SNP frequencies were first arcsine-transformed and then regressed on population latitude (measured as distance from the equator). The significance of the observed squared correlation coefficient, r2, was then estimated by generating 10,000 randomized data sets by binomial sampling under the expected frequency (the overall mean in the entire sample) of a SNP or haplotype. This generates 10,000 new frequencies for each subpopulation, for which 10,000 r2 values are then computed to determine the significance of the observed r2.
In addition, we performed an analysis to investigate the extent to which clinal variation at one site can be explained by the amount of linkage disequilibrium to another site as described by BERRY and KREITMAN (1993). In this approach, each site in turn is considered as the "governing" site, for which the clinal variation of every other "affected" site within a given locus may be explained by linkage to this site. For example, consider site X as the governing site and an affected site Y. For the entire pooled sample, the nucleotide T at site Y is present in 50% of the chromosomes in which the nucleotide A is present at site X and in 25% of the chromosomes that lack A at site X. If A is present at site X in 8 out of 12 chromosomes in a given subpopulation, the expected frequency of T at site Y in this subpopulation is (0.5 x 8) + (0.25 x 4) = 5/12. The expected frequency is computed in this manner for each individual subpopulation, from which 10,000 simulated frequencies are generated for each subpopulation. The significance is then determined by performing regressions on each of the 10,000 simulated sets of frequencies as described above. Thus, if the r2 falls within the 95% confidence interval of the simulated r2 values, the clinal variation of T at site Y may be explained by linkage with A at site X.
|
RESULTS |
|---|
|
TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
1 kb in intron 6 occurring twice in the sample (line 8 from KK and line 27 from CH) was partially sequenced. Representative polymorphism data are shown in Figure 2. Of the three nucleotide polymorphisms in the coding region, only one changes the amino acid sequence (Glu to Gln at position 1113 of the R1 fragment), and this occurs only once in the sample (line 95 from BOG). The estimates of average nucleotide diversity, and , at silent sites are low for each population (Table 2), on average >10-fold lower than estimates at 10 neutral loci in regions of normal to high recombination (fw = 0.00066; neutral = 0.0079; DAS et al. 2004). Notably, populations from the northernmost range of the sampled locations (Nepal, Myanmar, and Japan) show the lowest levels of diversity, the most extreme being Nepal, which is monomorphic at fw. The values of TAJIMA's (1989) D-statistic are negative in a majority of the populations, with the exception of those populations of more intermediate latitude, which show positive values. The D-value of the population from Java (BOG) significantly deviates from zero, although this may represent a genome-wide effect in this population as the values of D from the 10 neutral loci also significantly deviate from zero in this population (DAS et al. 2004). This interpretation is supported by the observation that three of the four populations from Sundaland surveyed show strongly negative D-values at fw, consistent with the observation at the 10 neutral reference loci.
|
|
55 comparisons], for each of the 13 sampled populations. For each population, the probability of observing at least i significant tests at the fw locus given that n paired tests were performed and k were significant between the l loci was calculated using Equation 1 (see MATERIALS AND METHODS). The number of comparisons deviating from the neutral expectation was significantly higher than expected for all northernmost populations (PUR, BBS, KATH, MAN, and KMJ), as well as several populations in the South (KK, DAR, and CEB). Thus, a constant-rate, neutral model of molecular evolution is rejected for these populations. These results are summarized in Table 3.
|
other = 0.00078). The haplotype classes in high frequency, in particular the northern class, harbor less variation (northern = 0.00024; southern = 0.00045). The geographic distribution of northern, southern, and other haplotypes is shown in Figure 3.
|
|
|
Although the overall scheme and rationale of our analysis of clinal variation at fw follows that of BERRY and KREITMAN (1993), our data set differs in an important way. Previous studies applying this design (BERRY and KREITMAN 1993; VERRELLI and EANES 2000) have focused on distinguishing and identifying the target(s) of clinal selection (e.g., sites such as amino acid polymorphisms displaying significant clinal variation that could not be explained by linkage to other sites were identified as putative targets). Although linkage disequilibrium should technically be calculated only for individual populations, extensive nonindependence between polymorphic sites exists across the entire surveyed region. In particular, the derived polymorphisms characterizing the northern and southern haplotypes are in complete linkage disequilibrium. This is not surprising, given that fw resides in a region of very low recombination (STEPHAN and MITCHELL 1992); the size of the region in which linked neutral variation is affected by selection may be very large. Given that 53 of 54 segregating mutations in this data set are silent and the single nonsynonymous mutation occurs only once in the sample, the target(s) of selection is unlikely to reside within the region sequenced in this survey. However, the analysis of clinal variation with respect to linkage disequilibrium to other sites applied to this data set is informative nonetheless, as it reaffirms that sites distinguishing the northern haplotype are responding to clinal selection in a nonindependent manner (Figure 5), most likely due to being linked to a target(s) outside of the sequenced region.
|
Test of the background selection model:
The above results of the HKA test indicate that for several populations, the level of polymorphism at fw is too low to be explained by a constant-rate, neutral model. Two alternative models proposed to explain the reduction of variability in regions of low recombination are the hitchhiking (MAYNARD SMITH and HAIGH 1974; KAPLAN et al. 1989; STEPHAN et al. 1992) and background selection (CHARLESWORTH et al. 1993; HUDSON and KAPLAN 1995; CHARLESWORTH 1996) models. The hitchhiking model describes the effect of rare, strongly selected beneficial mutations on linked neutral polymorphism, while the background selection model considers the effects of frequent, strongly deleterious mutation onlinked neutral variants. In the following, we applied the method of STEPHAN et al. (1998), which utilizes the unique prediction of background selection operating in a subdivided population to distinguish between these two alternative models. Because the effective size of local demes is reduced in regions of low recombination relative to that in regions of normal to high recombination, a smaller number of effective migrants is expected to increase FST (CHARLESWORTH et al. 1997).
To test the null hypothesis that background selection is responsible for the observed pattern of differentiation between pairs of populations throughout the D. ananassae species range, we generated a probablity density of FST values under the finite island model for k demes and a migration rate MS, mutation parameter S, and per locus recombination rate RS at the locus putatively under selection (fw). A range of values was chosen for the unknown parameters k and RS, while MS and S were estimated from the data (see MATERIALS AND METHODS). The probability of obtaining a value of FST less than or equal to the observed FST under background selection is given for representative pairwise comparisons between populations in Table 5. For several comparisons among populations in the North and among populations in the South, FST values are too low to be explained by the background selection model for various values of k and RS, whereas almost all remaining values within these regions approached significance. Although less conservative, higher values of k are likely more realistic for D. ananassae (DAS et al. 2004) and produced lower P-values. In addition, in contrast to the previous study of fw, evidence of intragenic recombination was found by the four-gamete rule (HUDSON and KAPLAN 1985) in this data set, indicating that a nonzero level of recombination may be appropriate, which also produces lower P-values. Thus, the low level of differentiation among populations within each of these two geographic regions may be indicative of the spread of positively selected alleles.
|
|
DISCUSSION |
|---|
|
TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
Selection vs. demography:
In addition to providing a control for nonadaptive processes in the analysis of clinal variation, detailed analysis of population structure based on10 neutral loci has revealed other interesting aspects of the population history of D. ananassae that shed light on the pattern of variation observed at fw (DAS et al. 2004). First, the method of VOGL et al. (2003) applied to these loci has enabled these populations to be characterized as either central or peripheral by the inference of the migration-drift parameter, 
P. In short, this is the probability that two sequences randomly drawn from a population coalesce before migration. High values of P are indicative of populations being highly differentiated due to drift (and thus peripheral), while low values indicate the population is closer to the central, ancestral species distribution (VOGL et al. 2003). The populations from five SE Asian localities [BKK, KL (Kuala Lumpur, not included in the fw survey), BOG, KK, and MNL] display high variability and low estimates of P and are inferred to be central populations likely representative of an ancestral population of D. ananassae (DAS et al. 2004). The other populations showed lower variability and higher estimates of P, indicating that these populations are more peripheral. Due to the consistent 10-fold lower variation at fw in comparison to the neutral loci, estimates of P are systematically higher at fw. However, the relative difference in these estimates between populations differs at fw and the 10 neutral loci in several cases (Figure 6). In particular, the CH population has one of the highest estimates of P at the neutral loci, in contrast to the lowest at fw. Thus, although CH appears to be one of the most peripheral of all the populations based on the neutral loci, a higher diversity of haplotypes is present at fw relative to the other populations. A peripheral status in combination with intermediate latitude may have left this population less subject to the effects of selection observed in other populations. The presence of the highest frequency (33%) of non-sweep-associated haplotypes in this population is consistent with this hypothesis.
|
Selective sweeps in a subdivided population:
Previous analysis of polymorphism at fw in four populations (Nepal, Myanmar, India, and Sri Lanka) considered several possible scenarios of a selective sweep in a subdivided population (CHEN et al. 2000). One possibility is that the pattern of homogenization of allele frequencies within, but differentiation between geographic regions [North (Nepal, Myanmar) and South (India, Sri Lanka)], was caused by independent selective sweeps in each region (the two-sweep model). Alternatively, if more than one haplotype became associated with the selected allele via recombination, differential migration of these two haplotypes could result in a similar pattern (the single-sweep model; SLATKIN and WIEHE 1998). A third scenario not mutually exclusive of the above two models is that of local adaptation, where a selective sweep may be restricted to certain regions of a species range.
The significantly expanded sampling of this current survey greatly facilitates distinguishing between alternative models. Similar to the study of CHEN et al. (2000), a pattern of homogenization within, but differentiation between geographic regions is observed. However, two important differences are the scale on which this is observed and the cline of allele frequencies between these two regions. The northern haplotype is fixed or in high frequency in all populations of higher latitude, and a cline of decreasing frequency is found throughout the entire sample. A similar pattern is observed with the southern haplotype, although the pattern of clinal variation is not as strong: the northern haplotype also decreases in frequency in the absence of high frequencies of the southern haplotype (e.g., in India); thus, the cline of southern haplotype frequency in the opposite direction may be a secondary effect (see Analysis of clinal variation and below). The model of SLATKIN and WIEHE (1998) predicts that differential migration of two different haplotypes linked to the same selected allele will lead to the fixation of only one of these haplotypes in any given population. In addition, should this single-sweep model be invoked, the selective advantage of the beneficial allele should also be necessarily unconditional. Thus, under this model, given that populations in the North and South are fixed or nearly fixed for their respective haplotypes, populations located in intermediate locations (e.g., CH, CNX, and BKK) should also be fixed for one haplotype or the other. In contrast to this prediction, the northern haplotype coexists with other haplotypes, the degree to which being determined by latitude. For this reason, the single-sweep model is unlikely to explain the data. Thus, it is most plausible that two independent sweeps have occurred in the northern and southern regions.
Given the strong evidence for clinal variation of the northern haplotype, it seems that minimally this sweep is a candidate for a locally favored substitution. We hypothesize that the regional high frequency of the southern haplotype is more likely due to the spread of an unconditionally favorable allele [i.e., some populations showing evidence of this sweep are part of the ancestral range of D. ananassae (DAS et al. 2004)], although this has not spread throughout the species range because a second, independent sweep associated with a locally favored allele has occurred in the North. Partial inconsistencies in the distribution of the northern haplotype (e.g., the Indian and the Philippine samples have similar latitudes but different composition of fw haplotypes) may at least in part be due to inconsistencies in environmental variables that correlate with latitude. For example, the central and southern Phillipine islands remain hot and humid all year round, while the Indian subcontinent experiences seasonal variation in temperature.
Target(s) of selection:
Traits such as cold tolerance are known to vary with latitude in several species, including D. ananassae (GILBERT and HUEY 2001), and it was recently shown that high-altitude Himalayan strains of this species have evolved a temperature dependency to the rhythmicity of eclosion (KHARE et al. 2002). Although the pattern of differentiation at fw suggests that positively selected mutations have occurred at linked sites, the size of the fragment displaying reduced variation may be quite large due to the low recombination of the region containing fw. Although numerous chromosomal rearrangements have occurred since D. ananassae and D. melanogaster last shared a common ancestor, gene order on a more local scale is more likely to be preserved. In D. melanogaster, fw lies in a region of normal to high recombination that is relatively gene rich (10 genes in a 100-kb window around fw). Thus, it is reasonable to expect that many potential targets of selection are linked to fw. The availability of the genome sequence of D. ananassae in the near future will greatly facilitate the identification of mutation(s) involved in this sweep(s), as well as provide the necessary background for studying adaptation at the genome level in another species. The parallels between the recent evolutionary history of the two cosmopolitan species D. melanogaster and D. ananassae (e.g., the invasion of temperate regions from an ancestral tropical environment) provide an exciting opportunity for comparative studies of adaptation at the genome level.
|
ACKNOWLEDGEMENTS |
|---|
|
TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
|
FOOTNOTES |
|---|
|
LITERATURE CITED |
|---|
|
TOPABSTRACTMATERIALS AND METHODSRESULTSDISCUSSIONACKNOWLEDGEMENTSLITERATURE CITED |
|---|
BERRY, A., and M. KREITMAN, 1993 Molecular analysis of an allozyme cline: alcohol dehydrogenase in Drosophila melanogaster on the east coast of North America. Genetics 134: 869–893.[Abstract]
CHARLESWORTH, B., 1996 Background selection and patterns of genetic diversity in Drosophila melanogaster. Genet. Res. 68: 131–149.[Medline]
CHARLESWORTH, B., M. T. MORGAN and D. CHARLESWORTH, 1993 The effect of deleterious mutations on neutral molecular variation. Genetics 134: 1289–1303.[Abstract]
CHARLESWORTH, B., M. NORDBORG and D. CHARLESWORTH, 1997 The effects of local selection, balanced polymorphism and background selection on equilibrium patterns of genetic diversity in subdivided populations. Genet. Res. 70: 155–174.[CrossRef][Medline]
CHEN, Y., B. J. MARSH and W. STEPHAN, 2000 Joint effects of natural selection and recombination on gene flow between Drosophila ananassae populations. Genetics 155: 1185–1194.
CROW, J. F., 1986 Basic Concepts in Population, Quantitative, and Evolutionary Genetics. W. H. Freeman, New York.
DAS, A., S. MOHANTY and W. STEPHAN, 2004 Inferring the population structure and demography of Drosophila ananassae from multilocus data. Genetics 168: 1975–1985.
DAVID, J. R., and P. CAPY, 1988 Genetic variation of Drosophila melanogaster natural populations. Trends Genet. 4: 106–111.[CrossRef][Medline]
GILBERT, P., and R. B. HUEY, 2001 Chill-coma temperature in Drosophila: effects of developmental temperature, latitude, and phylogeny. Physiol. Biochem. Zool. 74: 429–434.[CrossRef][Medline]
GLINKA, S., L. OMETTO, S. MOUSSET, W. STEPHAN and D. DE LORENZO, 2003 Demography and natural selection have shaped genetic variation in Drosophila melanogaster. Genetics 165: 1269–1278.
HARR, B., M. KAUER and C. SCHLöTTERER, 2002 Hitchhiking mapping: a population-based fine-mapping strategy for adaptive mutations in Drosophila melanogaster. Proc. Natl. Acad. Sci. USA 99: 12949–12954.
HUDSON, R. R., and N. L. KAPLAN, 1985 Statistical properties of the number of recombination events in the history of a sample of DNA sequences. Genetics 111: 147–164.
HUDSON, R. R., and N. L. KAPLAN, 1995 Deleterious background selection with recombination. Genetics 141: 1605–1617.[Abstract]
HUDSON, R. R., M. KREITMAN and M. AGUADé, 1987 A test of neutral molecular evolution based on nucleotide data. Genetics 116: 153–159.
KAPLAN, N. L., R. R. HUDSON and C. H. LANGLEY, 1989 The "hitchhiking effect" revisited. Genetics 123: 887–899.
KAUER, M. O., D. DIERINGER and C. SCHLöTTERER, 2003 A microsatellite variability screen for positive selection associated with the "Out of Africa" expansion of Drosophila melanogaster. Genetics 165: 1137–1148.
KHARE, P. V., R. J. BARNABAS, M. KANOJIYA, A. D. KULKARNI and D. S. JOSHI, 2002 Temperature dependent eclosion rhythmicity in the high altitude Himalayan strains of Drosophila ananassae. Chronobiol. Int. 19: 1041–1052.[CrossRef][Medline]
LACHAISE, D., M. CARIOU, J. R. DAVID, F. LEMEUNIER, L. TSACAS et al., 1988 Historical biogeography of the Drosophila melanogaster species subgroup, pp. 159–225 in Evolutionary Biology, edited by M. K. HECHT, B. WALLACE and G. T. PRANCE. Plenum, New York.
MAYNARD SMITH, J., and J. HAIGH, 1974 The hitch-hiking effect of a favourable gene. Genet. Res. 23: 23–35.[Medline]
NEI, M., 1987 Molecular Evolutionary Genetics. Columbia University Press, New York.
OAKESHOTT, J. G., J. B. GIBSON, P. R. ANDERSON, W. R. KNIBB, D. G. ANDERSON et al., 1982 Alcohol dehydrogenase and glycerol-3-phosphate dehydrogenase clines in Drosophila melanogaster on different continents. Evolution 36: 86–96.[CrossRef]
PRITCHARD, J. K., M. STEPHENS and P. DONNELLY, 2000 Inference of population structure using multilocus genotype data. Genetics 155: 945–959.
ROZAS, J., and R. ROZAS, 1999 DnaSP version 3: an integrated program for molecular population genetics and molecular evolution analysis. Bioinformatics 15: 174–175.
SLATKIN, M., and T. WIEHE, 1998 Genetic hitch-hiking in a subdivided population. Genet. Res. 71: 155–160.[CrossRef][Medline]
STEPHAN, W., and S. J. MITCHELL, 1992 Reduced levels of DNA polymorphism and fixed between-population differences in the centromeric region of Drosophila ananassae. Genetics 132: 1039–1045.[Abstract]
STEPHAN, W., T. H. E. WIEHE and M. W. LENZ, 1992 The effect of strongly selected substitutions on neutral polymorphism: analytical results based on diffusion theory. Theor. Popul. Biol. 41: 237–254.
STEPHAN, W., L. XING, D. A. KIRBY and J. M. BRAVERMAN, 1998 A test of the background selection hypothesis based on nucleotide data from Drosophila ananassae. Proc. Natl. Acad. Sci. USA 95: 5649–5654.
TAJIMA, F., 1989 Statistical method for testing the neutral mutation hypothesis by DNA polymorphism. Genetics 123: 585–595.
TOBARI, Y. N., 1993 Drosophila ananassae—Genetical and Biological Aspects. Japan Scientific Societies Press/Karger, Tokyo/Basel, Switzerland.
VERRELLI, B. C., and W. F. EANES, 2000 Extensive amino acid polymorphism at the pgm locus is consistent with adaptive protein evolution in Drosophila melanogaster. Genetics 156: 1737–1752.
VOGL, C., A. DAS, M. BEAUMONT, S. MOHANTY and W. STEPHAN, 2003 Population subdivision and molecular sequence variation: theory and analysis of Drosophila ananassae data. Genetics 165: 1385–1395.
WATTERSON, G. A., 1975 On the number of segregating sites in genetical models without recombination. Theor. Popul. Biol. 7: 256–276.[CrossRef][Medline]
This article has been cited by other articles:
 |
|
 |
|
  E. Eveno, C. Collada, M. A. Guevara, V. Leger, A. Soto, L. Diaz, P. Leger, S. C. Gonzalez-Martinez, M. T. Cervera, C. Plomion, et al. "Contrasting Patterns of Selection at Pinus pinaster Ait. Drought Stress Candidate Genes as Revealed by Genetic Differentiation Analyses" Mol. Biol. Evol., February 1, 2008; 25(2): 417 - 437. [Abstract] [Full Text] [PDF]
|
|
|
|
 |
|
 M. D. Schug, S. G. Smith, A. Tozier-Pearce, and S. F. McEvey The Genetic Structure of Drosophila ananassae Populations From Asia, Australia and Samoa Genetics, March 1, 2007; 175(3): 1429 - 1440. [Abstract] [Full Text] [PDF]
|
|
|
|
|
|
A. Vasemagi The Adaptive Hypothesis of Clinal Variation Revisited: Single-Locus Clines as a Result of Spatially Restricted Gene Flow Genetics, August 1, 2006; 173(4): 2411 - 2414. [Full Text] [PDF]
|
|
|
|
|
|
J. M. Braverman, B. P. Lazzaro, M. Aguade, and C. H. Langley DNA Sequence Polymorphism and Divergence at the erect wing and suppressor of sable Loci of Drosophila melanogaster and D. simulans Genetics, July 1, 2005; 170(3): 1153 - 1165. [Abstract] [Full Text] [PDF]
|
|
| ||||||||||||||||||||||||||||||||||||||||||||||||||||||||||||||
| HOME | HELP | FEEDBACK | SUBSCRIPTIONS | ARCHIVE | SEARCH | TABLE OF CONTENTS |
