Copyright 0 1996 by the Genetics Society of America Sexual Reproduction Playsa Major Role in the Genetic Structure of Populations of the Fungus Mycosphaerella graminicola Ruey-Shyang Chen and Bruce A. McDonald Department of Plant Pathology and Microbiology, Texas A H M University, College Station, Texas 77843-2132 Manuscript received March 13, 1995 Accepted for publication January 10, 1996 ABSTRACT The relative contributionsof sexual and asexual reproductionto the genetic structureof populations can be difficult to determine for fungi that use a mixture of both types of propagation. Nuclear RFLPs and DNA fingerprints wereusedtomake indirect and direct measures of departures from random mating in a population of the plant pathogenic fungusMycosphaerella graminicola during the course of an epidemic cycle.DNA fingerprints resolved 617 different genotypes among 673 isolates sampled from a single field overa %month period.Only 7% of the isolates represented asexual clones that were found more than once in the sample. The most common clone was found four times. Genotypic diversity averaged 85% ofits maximum possible value during the courseof the epidemic. Analysesof multilocus structure showed that allelic distributions among FWLP loci were independent. Pairwise comparisons of alleles at these loci were in gametic equilibrium. between individual RFLP loci showed that the majority Though this fungus has the capacity for a significant levelof asexual reproduction,each analysis suggested that M . graminicola populations maintaina genetic structure more consistentwith random-mating over the course of an epidemic cycle. F UNGI use a wide array of reproductive strategies in natural populations (ANDERSON et al. 1992), often including alternatingcycles of sexual and asexual reproduction. The genetic structure of fungal populations will be affected by the relative contributions of sexual and asexual reproduction to each generation. Populations that are largely asexual will exhibit a high degree of clonality, withfew genotypes present at relatively high frequencies. Random mating (sexual) populations are expected to display a high degree of genotypic diversity. The balance between sexual and asexual reproduction will be affected by the availability ofcompatible sexual strains, alternate hosts (as for some rust fungi), and suitable climatic regimes (LEUNG et al. 1993). The relative contributions of sexual and asexual reproduction to the genetic structure of fungal populations often are poorly understood (KOHN1995). BURDON and ROELFS(1985) used isozymes to show that sexual populations of Puccinia graminis f. sp. tn'tici from the Pacific Northwest had greater genotypic diversity than asexual populationsfromtheCentral Plains. BROWNand WOLFE(1990) used temporal changes in gametic disequilibrium between pairs of virulence genes and fungicide resistance to estimate the fraction of an Erisyphe graminis f. sp. hordei population that originated from sexual spores. In both of these cases, the sexual stage was known to play an important role in the life cycle of the fungus, and the authorsconfirmed the Cmresponding authm: Bruce A. McDonald, Department of Plant Pathology and Microbiology, Texas A&M University, College Station, T X 778432132, E-mail: b-mcdonald@tamu.edu Genetics 142: 1119-1127 (April, 1996) impact of sexual reproduction on thegenetic structure of populations. For many plant pathogenic fungi,however, it is not clear whether asexual or sexual reproduction plays the major role in determining the genetic structure of populations. This is especiallytrue forfungi that do not have a recognized sexual stage. In many cases, asexual reproduction is thought to occur more frequently than sexual reproduction because a limited number of clones or clonal lineages are widespread throughout agricultural fields over a wide geographical et al. 1994; KOHLI et range (LEVYet al. 1991; GOODWIN al. 1995). However, repeated sampling of a few clones that are found at high frequency because of strong selection or random drift can obscure the contribution of a sexual cycle to the genetic structure of these populations (LEUNGet al. 1993; KOHN 1995;MCDONALDet al. 1995). In addition,estimates of the relative degrees of sexual and asexual reproduction may be affected by differences in the dispersal distances of sexual and asexual spores and by the spatial scale used for sampling. For example, if asexual spores are dispersed only over short distances (e.g., centimeters), theasexual fraction of a populationmay not be adequately represented if sampling is conducted at a largerscale (e.g., meters). During the past five years, DNA-based genetic markers have become widely used to analyze the genetic structure of fungal populations (KOHNet al. 1991; LEVY et al. 1991; GOODWIN et al. 1992; MILGROOMet al. 1992; BOEGER et al. 1993; MCDONALD et al. 1994; KOHLIet al. 1995). These surveys have shown that fungal populations are not invariably clonal but can occupy a spectrum of population structures ranging fromhighly out- 1120 R.-S. Chen and B. A. McDonald crossing to almost strictly clonal. RFLPs in nuclear and mitochondrialgenomes have beenusedtoestimate gene and genotypic diversity within and among populations. DNA fingerprinting has been used to distinguish among different asexual lineages in a population. The advent of DNA markers that assay genotypic variation directly has made it possible to measure the relative impact ofsexual and asexual reproduction using a combination of direct and indirect measuresof the degree of random mating in populations. The direct measures are based o n using DNA fingerprints to estimate the fraction of a population that is genetically identical because of asexual reproduction. Indirect measures are based on measuring nonrandom associations among loci, such as gametic disequilibrium. Mycosphaerella graminicola (Fuckel) J. Schrt. in Cohn (anamorph Septon’a tn’tici Roberge in Desmaz.) is a haploid, ascomycete fungus that infects wheat worldwide (KING et aZ. 1983). The fungus produces airborne sexual ascospores that have the potential to disperse over long distances (kilometers). Rainsplash dissemination of the asexual spores presumably occurs over relatively short distances (meters). Several epidemiology studies have suggested that ascospores were the primary inoculum and ROYLE1987,1989; that colonize wheatfields (SHAW SCHUH 1990), while asexual pycnidiospores were thought tobe the main source of subsequent secondary infection.Theteleomorph(sexualstage)hasbeen found in several countries (SANDERSON and HAMPTON 1978; Scorn et al. 1988; GARCIA a n d MARSHALL 1992), but it was not clear how sexual reproduction affected the genetic structure of the population. Based o n results from a previous study (MCDONALDand MARTINEZ 1990a), we hypothesized that the initial infections resulted from airborne sexual ascospores and subsequent infections resulted fromsplash dispersal of asexual pycnidiospores. Under this hypothesis, we expected that the genetic structure of the population would become more clonal over the courseof an epidemic cycle. The main objectives in this experiment were to determine whether the genetic structure of a M . graminicola population was more consistentwith random matingor asexual reproduction and to determine whether the effect of asexual reproduction on genetic structure increased over the course of an epidemic cycle. MATERIALSANDMETHODS Fungal isolates: Isolates of M. gruminicolu were collected from a field experiment conducted on the Oregon State University Experimental Farm near Corvallis, OR. In October 1989, four wheat varieties that differed in resistance to M. gruminicolu were planted in pure stands and in all possibletwo, three-, and four-way variety mixtures (15 treatments total) in a randomized complete block designwith three replications. The field sitewas fallow in the year before initiating the experiment. Individual plots in the field measured 1.5 X 6.1 m in size. Natural infection was distributed uniformly through the field by mid-December. We believe that the initial infection came from ascospores originating from stubble in wheat fields 80 km distant from the field site. The plots were sampledon March 6 and May 30, 1990, hereafter referred to as early and late season, respectively. Twentyinfected leaves were chosen randomly along two transects running across the length of each plot. The average distance between collections was 50 cm within each plot. The infected leaf tissue was air dried at room temperature for 2 weeks before making isolations. Only one isolation was made from each infected leaf. A total of 149 isolates were obtained from early in the season and 562 isolates were obtained from late in the season. Sample sizes were <900 isolates for both collections because some leaves did not possess viable fungal fruiting bodies and limitations in funding restricted the number of isolates that could be assayed. DNA extraction, probes, and hybridization: DNA wasextracted from each isolate using a CTAB extraction protocol described previously (MCDONALDand MARTINEZ 1990b). Punfied DNA (4 pg) was digested individually with the restriction enzymes PstI or XhoI. DNA fragments were separated on 0.8% agarose gels and then transferred to nylon membranes using the alkaline transfermethod (REED and MANN 1985) as recommended by the manufacturer (BioRad, Hercules,C A ). Development of anonymous DNA probes used for RFLP analysis was described previously (MCDONALDand MARTINEZ 1990b). The source of these probes was a partial Suu3A diges tion of total DNA from S. tritici. DNA fragments ranging from 500-2500bpinsizeweresize-fractionated before cloning into a pGEM4 (Promega, Madison, WI) plasmid vector. Four hundred randomly chosen clones were kept for use as probes. Based on an initial screen, 10 probes that hybridized to single two loci loci, and one probe that hybridized simultaneously to located on different chromosomes (MCDONALDand MARTINEZ 1991a,b) were used. Together these probes hybridizedto loci on 12 of the 18 chromosomes in the M. graminicola genome (MCDONALD and MARTINEZ 1991a; B. A. MCDONALD, unpublished results). Two probes (pSTL40 and pSTL70) that hybridized to dispersed, repetitive DNA sequences were also usedinthisstudy. The repetitive probes wereshown previously to be useful for DNA fingerprinting (MCDONALDand MARTINEZ 1991b). Probes were labeled by nick translation following the manufacturer’s recommendations (BRL, Gaithersburg, MD). Data analysis: Each probeenzyme combination was defined as a different RFLP locus. DNA fragments or combinations of fragments with different sizes were treated as alleles at each RFLP locus. Only PstI was used to digest DNA from the late-season collection to lowerthe cost of collecting data. As a result, there are larger sample sizes for all RFLP loci that use PstI than for RFLP loci that use XhoI. Isolates having the samemultilocushaplotype (i.e., having the samealleles at each of the single RFLP loci) were compared using DNA fingerprints. Isolates having the same multilocus haplotype and DNA fingerprint were assumedto be individual members of the same clone (MCDONALDand MARTINEZ 1991b). Based on frequencies of alleles at individual loci, and frequencies of individual fragments in DNA fingerprints, the probability that two individuals wouldhave the same DNA profile by chance was <lo-’ on average in this population (B. A. MG DONALD,unpublished observations). To determine whether repeat sampling of the same clone would s e c t measures of association among loci, a second “clonecorrected” data set was constructed by including only one representative of each clone for each analysis of gametic disequilibrium. The measure of genotypic diversity (STODDART and TAYLOR 1988) was based on the number of isolateswith different multilocus haplotypes and DNA fingerprints in each collection. Only isolates with the full complement of single-locus 1121 Sexual FungiReproduction in RFLP data and fingerprints were included in this analysis. Genotypic diversity ineach collection was measured usingthe formula e= 1 c CCfX) * WN)*I X=O where N is the sample size and fx is the number of genotypes obsepled x times in the sample. The maximum possible value for G, which occurs when each individual in the sample has a different genotype, is the number of individuals inthe sample. To compare G in collections with different sample sizes, we divided G from each collection by N to calculate the percentage ofmaximumpossiblediversity that was obtained (CHENet al. 1994).A t-test was used for statistical comparisons between the normalized measures of G (CHENet al. 1994). The method suggested by BROWNet al. (1980) was used to measure multilocus associationsamong all loci based on the variance of heterozygosity. Gametic disequilibrium between pairs of loci was calculated using the following methods suggested by WEIR(1990).A test for significance of the disequilib rium coefficient across all alleles for each pair oflociwas formulated with the chi-square test statistic for all pairs of alleles u and v, which were present at loci that had k and 1 alleles total, respectively. n was the number of individuals inthe sample and B,,,,was the maximum likelihood estimator for the coefficient of disequilibrium between alleles u and v. The observed allele frequencies for the loci were pu and p,, respectively. This chi-square statistic had (k - 1) ( I 1) degrees of freedom for each pairof loci. We observed that tests basedon pairs ofrare alleles at the two loci often resulted in a significantvalue for the chi-square testas a resultof a low expected number in the denominator. This sometimes led to a rejection of the null hypothesis of independence when only one or two rare allele pairs were in disequilibriumout of 6070 allele pairs intypical a locus-by-locuscomparison.To correct forthisbias,allelespresent at a frequency of <lo% were pooled into a single category for comparisonstheinlate-season collection ( N = 562) and alleles at a frequencyof <20% were pooled in the early-season collection ( N = 149). A test for the significance of the disequilibrium coefficient between each pair of alleles at two loci was formulated with the chi-square statistic 4 w x;" = Pu(l- P,)P"(l - P") This chi-square statistichad one degree of freedom. As before, all allelespresent at frequencies of <10 and 20% in the lateand early-season populations, respectively, were pooled into a single category. Pairs of allelesthat showed a significant( P < 0.05) departure from random expectations weretested further with Fisher's exact testof independence (WEIR1990). The two-tailed exact test for independence between pairs of alleles at different loci was calculated with the computer program FISH 6, version 1.001(ENGELS1988). In each exact test, all alleles except for the tested allele pairs were pooled into a single category.The level of significance usedfor the exact test was P < 0.05. RESULTS To make direct measures of the asexual fraction present in each sample, only the 673 isolates that had com- " ' 1 " - 4 " , . I ." d 9 . FIGURE 1.-Examples of DNA fingerprints and RFLPs in nuclear DNA of Mycosphaerelkz graminicokz isolates sampled from a single plot late inthe epidemic. The same isolatesare shownin each panel. All DNA was digested with PstI. (A) Probe pSTL70 hybridizesto a dispersed repetitive DNA family. Arrows indicate pairs of isolates with the same DNA fingerprints. (B) Probe pSTS192 hybridizes to two loci located on different chromosomes. The upper bands represent alleles at one locus and the lower bands represent alleles at a second locus. (C) Probe pSTS43 hybridizes to one locus. (D) Probe pSTL2 hybridizes to one locus. plete multilocus haplotypes were compared by DNA fingerprints to differentiate clones among isolates. There were several casesin which isolateshad thesame multilocus haplotypes but different DNA fingerprints. In these cases, the isolates with different DNA fingerprints represented differentclones. All isolates that had the same DNA fingerprint had thesame multilocus h a p lotype. The frequency distributions of isolates having the same multilocus haplotypes or DNA fingerprints in the early- and late-season populations are shown in Table l. There were two cases where isolates withthe same DNA fingerprints were found both early and late in the season (CHENet al. 1994). In one of these cases, the clones were found in different, neighboringplots, demonstrating that asexual spores can move 2 1 m over the course of an epidemic. In theother case, the same clone was sampled four times from the same plot, twice early and twice late in the season. Based on DNA fingerprints, 617 different genotypes were found among673 isolates sampled. Only 7% of these genotypes were found more andR . 4 . Chen 1122 TABLE 1 Frequency distributionof genotypes in early and late season populations of Mycosphaere22a graminicola in the Oregon field experiment Multilocus haplotypes" DNA fingerprintsb Late Early Late Early X" season season season season 1 2 3 4 5 Total number of genotypes Total number in sample ( N ) e. ( G / N )%" 80 14 4 1 112 1 387 42 14 4 1 0 1 0 100 448 120 497 129 78.1 60.5% 544 384.3 70.6% 129 111.7 86.6% 544 449.8 82.7% 7 459 30 7 1 0 Multilocus haplotypes were differentiated by combining the alleles present at 11 and 12 individual RFLP loci in the early- and late-season populations, respectively. bDNA fingerprints were based on hybridization of probe pSTL40 and pSTL70 to DNA from each isolate. Number of times each genotype is present in the population. Index of genotypicdiversity G (STODDART and TAYLOR 1988). "The percentage of maximum possible value for G. than once in the sample. Two measures of genotypic diversity were made from these data. From the multilocus haplotype data, 60.6 and 70.7% of the maximum possible valueswere found in theearly- and late-season populations, respectively. These valueswere not significantly different ( P = 0.54). Based on the DNA fingerprint data, 86.6 and 82.7% of maximum possible values were found in the early-and late-season populations, respectively ( P = 0.72). Though the DNA fingerprintsdetectedmore genotypic diversity thanthe multilocus haplotypes, the difference between the two values was not statistically significant ( P = 0.14 for lateseason haplotypes us. fingerprints). Table 2 summarizes multilocus associations among RFLP loci in the M . graminicola population based on the method of BROWNet al. (1980). Allsix subsets of the data had an adjusted value of S; that exceeded p(2), supporting independence of loci. Statistically significant increases in multilocus associations (SE exceeding L) were notfound in any population, suggesting that allele distributions among RFLP loci were independent. \'slues of X(2), the measure of intensity of multilocus association, were low ranging from 0.016 to 0.095 among populations.Values of X(2) were higher in the clonecorrected data, but there were no significant differences among any data sets. WEIR'Smeasures of gametic disequilibrium for the B. A. McDonald entire population are summarized in Table 3. Only the sixRFLP loci common to both early- and late-season collections were used in this analysis. Pairwise comparisons for gametic disequilibrium between RFLP loci were measured for all isolates (uncorrected) included in the data set or only one representative of each clone (clonecorrected). For the 15 pairwise comparisons among loci in the uncorrected data,one pair of loci was in disequilibrium (5% level). In the clone-corrected data, all of the loci were at gametic equilibrium. Allele-by-allele comparisons were significant in 12 of 132 cases in the uncorrected and 14 of 132 comparisons in the clonecorrected data. However, only nine cases (7%) in the uncorrected data and nine cases (7%) in the corrected were significant at the 5% level with Fisher's exact test. In the early-season population, eight out of 55 pairwise comparisons from the uncorrected and seven comparisons for the corrected data were significant at the 5% level (Table 4). In the uncorrected samples, 43 of 306 allele-by-allele comparisons were significant at 5% level, but only nine (3%) of these comparisons were significant with Fisher's exact test. Inthe clone-corrected samples, 37 of 306 allele-by-allele comparisons were significant at 5% level, but only five (2%) of these comparisons were significant with Fisher's exact test. Table 5 shows the measures of gametic disequilibrium in the late-season population. Significance at the 5% level was found among six of the 66 possible painvise combinations from the uncorrected data, and only four of these comparisons were significant in the clonecorrected data. Allele-by-allele comparisons showed that 64 and 54 of 623 cases in the uncorrected and clonecorrected data, respectively, were significant at the 5% level and 37 (6%) and 24 (4%), respectively, were significant with Fisher's exact test. DISCUSSION DNA fingerprints and tests for departures from gametic equilibrium among single copy RFLPprobes were used to made direct and indirect assessments of the relative importance of sexual and asexual reproduction on thegenetic structureof a M. graminicola population. Direct measures of the amountof asexual reproduction based on DNA fingerprints showed that a low degree of clonality existed in the M . graminicola population during the course of an epidemic cycle. This suggested that the genetic structure of this M. graminicola population was dominated by outcrossing. Despite the potential for a significant amount of asexual reproduction, 617 differentnuclear DNA genotypes were found among 673 isolates. Many M. graminicola isolates had the same multilocus haplotypes, formed by combining 11- 12 individual RFLP loci at one time, while their DNA fingerprints were different. An average of 20 fragments was found for the DNA fingerprints, suggesting that more loci were being sampled by the probes that in Sexual Reproduction 1123 Fungi TABLE 2 Multilocus association among RFLP loci in an Oregon population of MycaSphaereUu gmminicola Population Uncorrected data Whole year Early season Late season Corrected data'' Whole year 140 Early season Late season rn n h P(2) L s: 342) 6 11 12 71 1 149 562 0.373 0.344 0.438 1.095 1.843 2.505 1.205 2.253 2.672 1.113 1.983 2.633 0.016 0.076 0.051 6 11 12 655 0.370 0.349 0.436 1.094 1.844 2.51 1 1.204 2.268 2.814 1.143 1.934 2.760 0.045 0.054 0.099 515 From BROWNet at. (1980). rn = number of RFLP loci; ?z = number of isolates sampled; h = mean single-locus diversity; p ( 2 ) = expected central moment, under Ho; L = upper 95% confident limit; Sz = observed variance of the number of heterozygous comparisons; X(2) = nleasures of multilocus structure. Data corrected for clonal fraction in the population based on DNA fingerprints. (1 hybridized to dispersed, repetitive sequences. These results confirmed our previous observations (MCDONALD and hlARTINEZ 1991b; BOECERet al. 1993) that DNA fingerprints have greater resolution to identify clones than multilocus haplotypes. Based on DNA fingerprints, 571 (93%) of the 617 different genotypes were unique. No clone was observed at a high frequency and themost common genotype was present only four times in either the early- or late-season populations. The clonal fraction was similar early and late in the season. By STODDART'S measure, genotypic diversity was 85% of' its maximum possible value on average and there was not a significant difference between the amount of' diversity found early and late in the epidemic. The findings of a large number of different genotypes and a high degree of genotypic diversity suggested that these M . graminicola isolates originated from a sexually reproducingpopulation. The finding that theclonal fraction did not significantly increase from the early to late season suggests that asexual reproduction did not have a significant impact on the genetic structure of the population over the course of the epidemic cycle. In a large random-mating population, neutral, un- linked loci are expected to be at gametic equilibrium. Statistical measures of departures from gametic equilibrium may provide indirect indicators of the relative importance of sexual and asexual reproduction. To determine the effect of repeated sampling of the same clone on measures of disequilibrium, we analyzed the data using either all isolates, called the uncorrected sample, or only a single representative of each genotype, called the clone-corrected sample. The purpose of using a clonecorrected sample was to eliminate artificial associations among loci that result from multiple sampling of the same clone. In Neissm'u meningztidis, MAYNARD SMITHet al. (1993) found that there was a significant degree of gametic disequilibrium when688isolates were compared, but when the 331 electrophoretically distinct genotypes were used, they appeared to be nearly indistinguishable from a panmictic population. In a California population of M . graminicola, 22 different clones were present in a sample of 93 isolates originating from 19 leaves (MCDONALDet al. 1995). Gametic disequilibrium was found among 76% of pairwise combinations of 12 RFLP loci when all 93 isolates wereused in the analysis. In the clone-corrected sample of22 isolates, significant disequilibrium was found for only TABLE 3 Measures of gametic disequilibrium among pairs of RFLP loci in whole-year population of Mycosphaerella gmminicola collected from a wheat cultivar mkture field experiment pSTS192-PstIA pSTS192-PstIB pSTS192-PstIA pSTS192-PstIB pSTS 14PstI pSTS2-PstI PSTLlO-PstI pSTL53PstI 0/4 NS 0/6 NS 2/6 (1) NS 2/6 (0) NS 2/10 (2) NS pSTS14PstI PSTLlO-PstI pSTS2-PstI pSTL53-Pd 0/4 NS 0/6 NS 0/6 NS 0/6 NS 1/6 (0) NS 0/6 NS 1/10 (0) NS (2) 2/9 (2) NS 0/9 NS 3/15 (3) NS 2/6 (1) NS 0/6 NS 2/9 NS 1/6 (0) NS 1/10 ( 1 ) NS 0/6 NS 0/10 NS 0/9 NS 4/15 (4)* 1/9 (0) NS 0/15 NS (1) 1/15 NS 1/15 (1) NS 0/9 NS 0/15 NS Numbers below the diagonal are measures of disequilibrium calculated using only a single representative of each clone (clonecorrected). Numbers above the diagonal were calculated with all isolates (uncorrected). The top entry shows the number of significant (P< 0.05) chi-square tests between individual alleles at different RFLP loci per the total number of tests made with the number of tests that were also significant with Fisher's exact test in parentheses. The bottom entry shows the results of a chi-square test for the significance of association between all alleles at the two loci: NS, not significant; * P < 0.05. 1124 R . 4 . Chen and B. A. McDonald TABLE 4 Measures of gametic disequilibrium among pairs of RFLP loci in early-season population of Myco+huerella graminicola collected from a wheat cultivar mixture field experiment pSTS192XhoIA pSTS192- pSTS192PstIA pSTS192PstIB pSTS14 PstI 4/4 0/4 (0) 0/4 0/6 NS 0/4 NS 0/4 NS 0/4 NS 2/4 (0) NS 0/4 NS 4/4 (0) ** XhnIA pSTSl92XhnIB pSTS192PstIA pSTS192PstIB pSTS14 PstI pSTSI96Xhd pSTS2PstI pSTL2XhoI pSTL10PstI pSTL.53. XhoI pSTL.530/4 PstI pSTS192XhnIB 4/4 (0) ** 0/4 NS 0/4 NS 0/4 NS 0/6 NS 0/6 NS 1/6 (1) * 0/6 NS 2/40/4 (0) NS ** 3/4 (0) ** 0/4 NS 2/4 (0) NS 2/6 (0) NS 2/6 (0) NS 1/6 (0) NS 4/6 (0) ** 0/4 NS 0/4 NS NS 4/4 (0) NS 0/4 NS 0/4 NS 0/6 NS NS 0/6 NS 0/6 NS 2/6 (0) NS NS 0/4 0/4 NS * 4/4 (0) * 0/6 NS 0/6 NS 1/6 (0) NS O/fi NS 014 NS 0/4 NS 0/6 NS 0/6 NS 0/6 NS 0/6 NS 0/4 NS NS pSTS196XhnI NS 0/6 NS 0/6 NS 0/6 NS 0/6 NS 1/9 (0) NS 0/9 NS 0/9 NS 0/6 NS 0/6 NS pSTS2PstI pSTL2XhnI pSTL10PstI pSTL53XhoI pSTL53PstI 0/6 NS 2/6 (0) NS 0/6 NS 0/6 NS 2/6 ( 1 ) 0/6 NS 4/6 (0) 2/4 (0) NS 0/4 NS 0/4 NS 0/4 0/4 4/6 (4) NS 1/9 (0) 0/9 NS 0/9 (0) NS 0/6 NS 0/6 NS * 1/6 (0) NS 0/6 NS 1/6 (0) NS 0/6 NS 0/9 NS 0/9 NS * 2/6 (0) NS 0/6 0/4 NS 0/6 NS 0/9 NS 0/9 NS 2/9 (0) * 2/9 (0) * 0/6 NS 2/6 (1) NS 0/6 NS 0/6 NS NS 0/4 NS 0/6 NS 0/6 NS 0/6 NS 1/6 (0) NS NS 0/4 NS 0/4 NS NS 0/4 NS 0/6 NS 0/6 NS 3/6 ( 1 ) * 0/6 NS 4/4 (3) ** 4/4 (3) ** Numbers belowthe diagonal are measuresof disequilibrium calculated using only a single representativeof each clone (clonecorrected).Numbers above the diagonal were calculated withall isolates (uncorrected).The top ently row shows the number of significant ( P < 0.05) chi-square tests between individual alleles at different RFLP loci per the total number of tests made with the number of tests that were also significant with Fisher’sexact test in parentheses. The bottom ently shows the results of a chisquare test for the significance of association between all alleles at the two loci: NS, not significant; * P < 0.05; ** P < 0.01. 12% of the painvise combinations. On average, nearly five isolations were made from each leaf in the California population. The majority of isolates that had the same DNA fingerprint were sampled fromdifferent fruiting bodies in a single lesion or different lesions on the same leaf. This analysis of the California population showed how the scale of sampling can affect the interpretation of the contribution of asexual reproduction to a population. In the case of M. gruminicolu, asexual reproduction may be significant on a small spatial scale (<1 m) as a result of the limited spread of the splashdispersed conidia. For the Oregon population described in this experiment, the difference in disequilibrium between the uncorrected and the clone-corrected samples was not significant. This probably is due to the fact that only a few clones were present in the Oregon population relative to the total number of isolates sampled. When collecting isolates in Oregon, only one isolate was taken from each leaf, which eliminated the possibility of sampling the same clone from the same leaf. We believe that the sampling method used in this Oregon experimentgave a more accurate measure of the influence of random mating on thegenetic structureof M. gruminicolu populations than the California population described previously (MCDONALDet ul. 1995). LENSKI (1993), who summarized several studies of the genetic structure of bacterial populations, pointed out that subdividing data on population structure into meaningful subsets based on electrophoretically distinct genotypes or geographic scales can reveal useful information. In R Zeguminosurum, subdivided data obtained on geographic basesshowed that both allelic diversity and linkage disequilibrium increased markedly with geographic distance (SOUZAet al. 1992). LENSKI (1993) also suggested that one must be cautious in accepting the joint inference that subsets are in linkage equilibrium where data sets as a whole exhibit clonality because a sufficiently subdivided data set may lose the statistical power to reject the null hypothesis of panmixia. In this study, the whole-year population and its two temporalsubpopulations, early- and late-season populations, were tested for gametic equilibrium. The results showed that temporal subdivision made no significant difference to the analysis, though more RFLP lociwere used in the analysis of the early- and lateseason populations than in the whole-year population. The data were also subdivided based on geographic separation (replications of complete blocks) and based on host treatment (wheat mixtures from which the fungal isolates originated). A comprehensive discussion of the differences among host treatments is beyond the scope of this paper. What is relevant here is that there were no significant differences in measures of genotypic 1125 Sexual Reproduction in Fungi TABLE 5 Measures of gametic disequilibrium among pairs of RFLP loci in late-season population of Mycosphmrella gmmimcola collected from a wheat cultivar mixture field experiment PstI PsdB pSTS192pSTS192PstIA pSTS14 pSTS196 pSTS2pSTL2- pSTLlO pSTL53- pSTS194 pSTS197pSTL31pST.543PstI Psa PstI pSTS192PstIA pSTS192PstIB pSTS14 PstI pSTS196 PstI pSTSBPstI pSTL2-Pstl pSTLl0PstI pSTL53PstI pSTS199PstI pSTS1907PSlI pSTL31PrtI ~ ~~~ Numbers below the diagonal are measures of disequilibrium calculated using only a single representative of each clone (clonecorrected). Numbers above the diagonal were calculated with all isolates (uncorrected). The top e n t ~shows the number of significant ( P < 0.05) chi-square tests between individual alleles at different RFLP loci per the total number of tests made with the number of tests that were also significant with Fisher’s exact test in parentheses. The bottom e n t shows ~ the results of a chisquare test for the significance of association between all alleles at the two loci: NS, not significant: * P < 0.05; ** P < 0.01. diversity or gametic disequilibrium among blocks or host treatments used in this experiment. There was no evidence for population subdivision among blocks or treatments, suggesting that subdivision by location or host treatment did not affect the analysis of disequilibrium. The hypothesis that allelic distributions among RFLP lociwere independent was not rejected ( S z did not exceed L ) for any of the samples tested (Table 2), suggesting gametic equilibrium in these populations. One drawback to this measure of multilocus structure is that it ignores the behavior of particular allelic combinations in the sample. It is possible that gametic disequilib rium only occurs for particular allele combinations as a result of selection. Therefore, we further tested the association between pairs of RFLP loci in the populations using chi-square tests. On average, -90% of locus pairs were at equilibrium for both uncorrected and clone-corrected data sets. The allele-by-allele comparisons also showed a low level (-3%) of disequilibrium among these RFLP loci. These results showed that the great majority of alleles at RFLP loci were randomly associated. All of these findings supported the hypothesis that these isolates originated from a random mating population. We conclude that genetic recombination must occur very often and that it plays a major role in the genetic structure of M. graminicola populations. Selection driven by host genotype is thought to play a dominant role in establishing the genetic structure of many plant pathogen populations. This selection may be especially strong in agroecosystems because genetically uniform resistant hosts areplanted over large areas. Under these conditions, particular combinations of virulence genes in the pathogen are expected to increase in frequency as a result of strong selection to match corresponding resistance genes in the host. This selection will lead to high levelsof disequilibrium among particular combinations of virulence genes as frequently described in the rusts and mildews (e.g., WOLFE and ~ O T 1982; T HOWaLLER and Q ) S T E R G h 1991; KOLMER1992). Inthese cases, it is often assumed that the associations among virulence loci result from strong selection to match particular combinations of resistance genes in host populations. It is also possible that much of this disequilibrium is maintained over extended periods of time and at arbitrary levels due to asexual reproduction rather than because of selection among particular loci (MCDONALDand MCDEFWOTT 1993). In a pathogenwith low levels ofsexual reproduction, selection will increase the frequency of particular clonal lineages having combinations of virulence genes that match resistance genes in the host. Under these conditions, clonal lineages can persist for many generations and plant pathologists are usually correct when they assume that isolates with the same virulence spectrum are identical by descent. When pathogens undergo limited sexual reproduction, plant breeders can exploit andR.S.Chen 1126 the limits on recombination of virulence genes by deploying new combinations of resistance genes into a single host genotype. This is the strategy that has been used successfully to control many of the cereal rusts in North America for several decades. In a pathogen with a high level of sexual reproduction, such as M. paminicola, every sexual generation produces new combinations of virulence genes that can be selected out by the corresponding host resistance genes. Under this scenario, fungal isolates having the same combinations of virulence genes may not have recent common ancestors and the assumption that a population is composed of a limited number of clonal lineages will be incorrect. A breeding program oriented toward pyramiding resistance genes intocommon varieties is likely to fail because the pathogen has the potential to rapidly recombine new combinations of matching virulence genes. In this case, plant breeders should pursue nonspecific resistance that often is inherited as a quantitative trait. Before deciding on a gene deployment strategy, plant breeding programs should consider the genetic structure of the pathogen population. 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