# Human population structure detection via multilocus genotype clustering

- Xiaoyi Gao
^{1}Email author and - Joshua Starmer
^{2}

**8**:34

https://doi.org/10.1186/1471-2156-8-34

© Gao and Starmer; licensee BioMed Central Ltd. 2007

**Received: **18 December 2006

**Accepted: **25 June 2007

**Published: **25 June 2007

## Abstract

### Background

We describe a hierarchical clustering algorithm for using Single Nucleotide Polymorphism (SNP) genetic data to assign individuals to populations. The method does not assume Hardy-Weinberg equilibrium and linkage equilibrium among loci in sample population individuals.

### Results

We show that the algorithm can assign sample individuals highly accurately to their corresponding ethnic groups in our tests using HapMap SNP data and it is also robust to admixed populations when tested with Perlegen SNP data. Moreover, it can detect fine-scale population structure as subtle as that between Chinese and Japanese by using genome-wide high-diversity SNP loci.

### Conclusion

The algorithm provides an alternative approach to the popular STRUCTURE program, especially for fine-scale population structure detection in genome-wide association studies. This is the first successful separation of Chinese and Japanese samples using random SNP loci with high statistical support.

## Background

Population structure analysis is important to genetic association studies and human evolutionary history investigations. Population structure may confound the population based genetic association studies, leading to false positive results and failure to detect true associations [1–4]. In studies of human evolution, populations are usually considered groups of interest and there has been a significant amount of work dedicated to learning about the relationships among modern populations [5–9].

Two major approaches have been proposed to detect population structure: distance-based clustering methods and model-based methods. Distance-based approaches utilize the proportion of allele sharing as distances between individuals and are not computationally demanding. Since some of the genetic information in the data is ignored, such as allele frequencies, critics have suggested that distance-based methods are not suitable for detecting fine population structure, even when many SNP loci are used [10]. Contrary to these assertions, in this paper we demonstrate the feasibility of using a distance-based method to detect fine population structures. Model-based methods use standard statistical methods to estimate population parameters, and usually assume Hardy-Weinberg equilibrium for each population. The inference may not be good in the presence of small sample sizes due to the inaccurate estimation of allele frequencies. Model-based inference also depends heavily on the modeling assumptions.

STRUCTURE is a popular model-based program using Markov chain Monte Carlo (MCMC) within a Bayesian framework [11]. However several issues in STRUCTURE have to be addressed carefully: missing data, the number of clusters, and the covergence of MCMC [12]. Moreover, STRUCTURE is computationally intensive. Recently, Purcell and Sham proposed to use the Expectation Maximization (EM) algorithm to detect population structure [13]. The EM algorithm is faster than STRUCTURE when many markers are involved in the calculation, but for large numbers of loci the computational load is still challenging. Both STRUCTURE and the EM algorithm assume that marker loci are in linkage equilibrium within subpopulations [11, 13], which restricts the number of SNP loci that can be used. Even the improved version of STRUCTURE (version 2.0), which accounts for admixture Linkage Disequilibrium (LD), does not handle background LD well [14].

Many recent studies have been devoted to the human population structure analysis using DNA genetic markers. Bowcock et al. used 30 polymorphic microsatellites to construct trees of human inividuals that reflect their geographic origin with a neighbor-joining algorithm [6]. Mountain and Cavalli-Sforza also used a neighbor-joining algorithm to study human evolutionary history using an average of 75 RFLPs per individual [7]. Pritchard et al. pointed out that distance-based methods may be heavily dependent on the distance measure and graphical representation used, and may not be used for fine statistical inference [11]. Rosenberg et al. used STRUCTURE to analyze 377 autosomal microsatellite loci in 1056 individuals from 52 populations, and identified six main genetic clusters [8]. However, the solutions for the East Asia group were variable across runs when they tried to estimate population structure for the main regions. Turakulov and Easteal used Ward's algorithm, with a score matrix of Euclidean distances of allele sharing, for population structure analysis and concluded that the distance-clustering algorithm may not be used to detect fine-scale population structure [10]. Shriver et al. used 8,525 autosomal SNPs and a neighbor joining algorithm to infer population substructure in four populations: African-American, European-American, Chinese and Japanese [9]. They found a bifurcation between clusters of 10 Chinese and 10 Japanese individuals but with weak bootstrap support. Purcell and Sham used an EM algorithm on population structure analysis and validated the algorithm using simulated data but they did not show its efficacy with real data sets [13].

In this paper we describe a distance-based algorithm, AW-clust (A llele sharing distance and W ard's minimum variance hierarchical clustering), to assign individuals to populations based on multilocus genotype data. The method is different from previous distance-based approaches in many respects. Bowcock et al. used a neighbor-joining method to construct a human evolutionary tree [6], while we use Ward's minimum variance to estimate sub-clusters. Turakulov and Easteal used an Euclidean distance measure of allele mis-matches [10], while we used the allele sharing distance directly. Nakamura et al. required all markers to be unlinked and estimated the number of subpopulations, *K*, by cross-validation and the *k*-means algorithm in order to construct the hierarchical cluster [15], while the AW-clust method does not have these restrictions. The AW-clust method also differs in how it updates the distance matrix. Furthermore, the AW-clust method does not assume Hardy-Weinberg equilibrium and linkage equilibrium among loci in sample population individuals. There is also a conceptual difference in estimating *K*, the correct number of populations. We view this as a variable that need not be determined in advance. Allowing *K* to vary gives researchers an opportunity to effectively define the resolution of their investigation in response to the particular problem they are addressing. If only rough distinctions need to be made between populations, the resulting tree can be examined at a high level. If the study requires highly refined distinctions, the tree can be examined at a low level. Once we had determined the number of SNP loci needed to differentiate populations, we used Tibshirani et al.'s gap statistic [16] to objectively verify *K*.

We applied the AW-clust algorithm to two large human SNP data sets from the HapMap project [17] and Perlegen [18]. The algorithm accurately assigns HapMap sample individuals to the corresponding ethnic groups and it is also robust to admixed populations when tested on Perlegen data. Despite the suggestion that distance-clustering analysis may not detect fine-scale population structure [10, 11], we have successfully differentiated Chinese and Japanese sample individuals using HapMap data. This is the first successful detection of fine-scale population structure as subtle as that between Chinese and Japanese with high statistical support using genome-wide random SNP loci. We anticipate that other closely related populations may be separated by similar approaches. Using a larger number of SNP markers, AW-clust has the power to accurately detect population structure and assign individuals to their ethnic group and shows that it is not be necessary to estimate allele frequencies or LD in order to differentiate populations.

## Results

### Results of simulation study

We found that both the number of SNP loci and the length of generations since isolation have a strong impact on the clustering results. When two populations had been isolated for time, *t* = 0.75 (scaled in terms of 2*N* generations), the mean ± standard deviation for the Classification Error Rates (CERs – see the Methods section for more details) were 0.01 ± 0.01, 0.05 ± 0.03 and 0.12 ± 0.05 using 200, 100 and 50 SNP loci respectively. For *t* = 0.05, the mean ± standard deviation for the CERs were 0.05 ± 0.03, 0.12 ± 0.05 and 0.22 ± 0.07 using 200, 100 and 50 SNP loci respectively. When the generations since isolation were relatively short, several hundred SNP loci may be insufficient to guarantee a low CER. When *t* = 0.015, the mean ± standard deviation for CER were 0.03 ± 0.02, 0.08 ± 0.03 and 0.17 ± 0.05 using 2000, 1000 and 500 SNP loci respectively. Therefore, the quality of separation is likely to be a function of *t*, the generations since isolation, and the number of SNP loci used. When *t* is long, a few loci are sufficient to guarantee a good separation. But when *t* is relatively short, a large number of SNP loci is required.

### Results from empirical data

*K*, was identified from the major clusters in the hierarchical cluster plot. These values for

*K*were then objectively verified using the gap statistic, in which three scenarios were considered. First, we considered three major populations in the HapMap data, CHB, YRI and CHB+JPT (CHB and JPT being indistinguishable), using 1,000 random genome-wide SNP loci. Second, only CHB and JPT individuals were included using 30,000 random SNP loci. Third, the three populations in the Perlegen data were considered using 1,000 random SNP loci. The gap statistic plots for each scenario are shown in Figure 7. The log (

*W*

_{ k }) estimations and gap curves are plotted in the left (Figure 7(a),(c) and 7(e)) and right panels (Figure 7(b),(d) and 7(f)), respectively. The observed and expected log (

*W*

_{ k }) are indicated in red and blue and marked by O and E separately for each

*K*ranges from 1 to 6. The gap curved is plotted in the format of

*Gap*(

*k*) ± standard deviation of log (

*W*

_{ k }). The optimal

*K*is the elbow point in the observed log (

*W*

_{ k }) plot, which corresponds to the maximizing point in the gap curve. From the plots, the estimated optimal

*K*for each scenario is 3, 2 and 3, respectively. Multiple runs gave similar results. Therefore, the observation of

*K*from the major clusters in the hierarchical cluster plot is reasonable and consistent with the gap statistic estimation.

## Discussion

To distinguish populations, the ideal loci are those that have an allele fixed in one population and absent in the other populations [19–21]. For the HapMap data, SNPs were sequenced in a small number of individuals, which means that SNPs with rare alleles are less likely to be discovered [22]. There are many measures for Ancestry Informative Markers (AIM), such as absolute allele frequency difference (*δ*), expected heterozygosity, *F* statistics (*F*_{
ST
}), informativeness for assignment (*I*_{
n
}) and informativeness for ancestry coefficients (*I*_{
a
}) [20]. We did not use any AIM estimates for SNP selection in this study because we thought that the AIM estimates from one data set may not be safely applied to other data sets if the reference sample size was not large enough. Despite our SNP ascertainment procedures, we obtained very good results for population structure detection using HapMap and Perlegen data sets. The implication of this work is that it is possible to tackle population structure issues in genome-wide association studies with a large number of markers. Instead of a special marker selection procedure, the AW-clust algorithm uses a large number of random genome-wide SNPs to ensure a sufficient number of informative makers for inferences. Subpopulations can be identified, and then association tests are applied to each homogeneous group of individuals.

There are two key parts in the implementation of the AW-clust algorithm. The first part is the ASD distance matrix between all pairs of individuals. This distance was chosen because it can be shown using Balding and Nichols's DNA profile match probability theory [23] that the expected ASD between individuals from different subpopulations is always greater than that between individuals from the same subpopulation using SNP markers [24]. Thus, the within and between population distances may hardly overlap when many genome-wide random SNP loci are used. Therefore it is possible to differentiate populations from the half-matrix of pairwise distances without explicitly estimating allele frequencies for each sub-population. It is through the accumulated effect of many SNP loci that population structure can be identified. The second part in AW-clust is Ward's minimum variance algorithm, becuase inference of population structure based on ASD is likely to be reduced to contrasting group means and minimizing within-group variance of ASD. Ward's minimum variance appraoch is particularly suited to our problem, where the correct number of subpopulations is not known in advance, and we need to minimize the increase in the within-group ASD variance each time an individual is added to a cluster.

The advantage of our algorithm is that, relative to model-based methods, it is fast. Therefore, it can be applied to data sets with large numbers of individuals and SNPs, such as occur in genome-wide association studies. It took less than one minute on a desktop computer (P4 3.0G CPU with 1 GB memory) to separate CHB and JPT using 20K random SNP loci. Kruglyak (1999) estimated that approximately 500,000 uniformly distributed markers are required for genome-wide association studies. It would be valuable if we can make full use of these SNP markers in association studies for population structure protection. The AW-clust algorithm provides a possible solution to this scenerio. The AW-clust algorithm does not assume Hardy-Weinberg equilibrium or linkage equilibrium in the sample population individuals, no special marker selection criterion is required, and the algorithm is robust to relatively small sample sizes.

One drawback with distance-based methods is that the distance measure and the clustering algorithm are somewhat arbitrary. If another definition of distance or clustering method are used, the clustering results may change, which may be a reason, in addition to relatively small number of SNP loci used, why some authors did not see a separation of Chinese and Japanese sample individuals in previous studies [9, 10]. A problem with Ward's minimum variance method is that it may or may not give the minimum possible error sum of squres over all possible sets of *K* clusters from the data units. However, Ward's solution is generally very good even if it is not optimal on this criterion [25]. We found that the classical multidimensional scaling (MDS) algorithm [26] can also be used to determine the ethnic clusters in the second stage of the AW-clust algorithm, which can be implemented in the standard statistical software package R using the *cmdscale* () function. Distance-based methods are criticized for being more suited to data exploration than to statistical inference [11]. However, we believe AW-clust could be effectively used as a first step in statistical inference. After using AW-clust to identify the major clusters, we can use Bayesian methods to calculate the posterior probabilities for individuals belonging to each different cluster. A general challenge for population structure analysis is to derive the correct number of subpopulations, *K*, and it is no different for the AW-clust algorithm. We view *K* as a variable instead of a fixed number and let researchers determine the most appropriate level of separation. For example, CHB and JPT are often grouped together for data analysis [17, 27]. However, these two samples can be separated and fall in different clusters using AW-clust, as shown in the results. It is subjective whether we would like to treat them as one group or two groups and *K* should be defined to fit the researcher's interests and as the data permits. One possible alternative to the subjective definition of *K*, is to define it using the gap statistic. It should be noted, however, estimating *K* is still more art than science, and depends on many factors, such as population distance, number of individuals in each population, number of markers, random replicates and the method used.

It is easy to separate genetically distant ethnic groups, such as CEU (60), YRI (60) and CHB (45) + JPT (44) in the HapMap data, AA (23), EA (24) and HC (24) in the Perlegen data (sample size is in parenthesis). Both STRUCTURE (version 2.1) and the AW-clust algorithm gave very good classification in these situations using several hundred of random SNP loci. But the burn-in period and number of iterations in STRUCTURE may not be easily decided. Different authors used different settings [8, 11–13, 20, 21, 28]. In our tests, it seems that these settings depend on the sample size, the number of loci, and the genetic distances among populations in order to get the correct number of populations, *K*. STRUCTURE easily found the correct *K* = 3 with 5,000 burn-in followed by 1,000 iterations when we tested it on CEU (60), YRI (60) and CHB (45) + JPT (44) using 200 random SNP loci. However, when we reduced the CHB sample size to 10 (CEU (60), YRI (60) and CHB (10)), we needed to set 10,000 burn-in and 10,000 iterations for STRUCTURE in order to get the correct *K* using 200 random SNP loci. Another challenging situation for STRUCTURE is fine-scale population structure detection, such as that between Chinese and Japanese. STRUCTURE assumes that marker loci are in linkage equilibrium within subpopulations [11], which theoretically puts a restriction on the number of SNP loci that we can use from the human genome data. Even when we ignored this assumption and used 10,000 random SNPs in STRUCTURE, it did not separate CHB (60), YRI (60), CHB (45) and JPT (44) simultaneously since CHB and JPT were predicted to be in one cluster. This contrasts with the AW-clust algorithm, which separated CHB and JPT into two different clusters. When we chose to run STRUCTURE on the pooled CHB (45) and JPT (44) using 5,000 random SNP loci with a 5,000 burn-in period followed by 1,000 iterations, STRUCTURE identified two major clusters from the posterior probabilities of *K*. But when we reduced the sample size for JPT from 44 to 20, STRUCTURE failed to identify the correct *K*, even with 10,000 iterations after a burn-in period of 10,000 were used. The AW-clust identified two major clusters for CHB and JPT in the above situations. Neither of the two methods worked well when we reduced the sample size for JPT from 44 to 10 individuals using 5,000 random SNP loci. However, AW-clust created two discrete clusters for CHB (45) and JPT (10) when we increased the number of SNP loci to 20,000. STRUCTURE may or may not find the correct number of clusters, *K*, in the fine scale population structure situations using random SNP loci especially when a population has a relatively small sample size, such as 5 or 10 individuals, in addition to the considerable computing time consumed. If accurate AIMs are available, a likelihood approach should work well when predicting an individual's ethnicity [29].

STRUCTURE usually requires multiple runs to check the convergence of MCMC (STRUCTURE manual) which requires substantial computing time when a large number of individuals and SNP loci are used. The admixture proportions for each individual, *Q*, is considered an advantage of STRUCTURE. However, in our test on the Perlgen data set (AA is an admixture population), the inferred ancestry of individuals, $\widehat{Q}$, may be sensitive to the number of SNP loci and sample sizes used. For example, we ran STRUCTURE with 50,000 burn-in followed by 50,000 iterations on AA(23), EA(24) and HC(24) using 5,000 random SNP loci. All EA individuals were predicted to have ~10% membership with HC, while most of the predicted HC membership in EA individuals went away when we used only 1,000 random SNP loci. With 50,000 burn-in and 50,000 iterations, nearly half of the AA individuals were predicted to have some EA membership, the majority of the EA individuals were predicted nearly pure EA membership, and most of the HC individuals were predicted nearly pure HC membership for the data AA(23), EA(24) and HC(24) using 1000 random SNP loci. Most of the AA individuals' EA membership either disappeared or was predicted to be much smaller when we reduced the sample size of AA from 23 to 5 and kept EA(24) and HC(24) using 1,000 random SNP loci. But when the sample size setting is AA(23), EA(5) and HC(24), EA individuals showed ~20% membership with HC. The apparent advantage of the AW-clust algorithm over STRUCTURE is for fine scale population structure detection with small sample sizes since a large number of SNP loci can be used and a relatively short computing time is required. The correct number of populations may be easily identified from the major clusters in the hierarchical plot rather than through multiple runs of rough estimation from MCMC posterior probabilities of *K*, which depend on many factors, such as the length of burn-in, iterations, convergence, and number of populations in the sample.

## Conclusion

In summary, the AW-clust algorithm provides efficient calculation and visually appealing results. It can produce highly accurate clustering and assign individuals correctly to populations. This algorithm successfully differentiated the CEU, YRI, and CHB+JPT sample individuals in the HapMap data set. It is also robust to the admixed population AA in the Perlegen data set, which covers AA, EA and HC sample individuals. Moreover, it can detect fine-scale population structure as subtle as that between CHB and JPT. We anticipate that other closely related populations can also be separated by similar approaches. Our method combined with SNP markers has considerable power in population structure analysis and it is not necessary to estimate allele frequencies in order to differentiate populations.

## Methods

### Data

SNP data were drawn from the HapMap project Phase I and the Perlegen SNP data sets. In the HapMap Phase I SNP data, about 1.1 million SNPs were genotyped genome-wide from 269 individuals from four ethnic populations: 90 individuals (30 trios) from Yoruba in Ibadan, Nigeria (YRI), 90 individuals (30 trios) from CEPH in Utah residents with ancestry from northern and western Europe (CEU), 45 unrelated Han Chinese from Beijing, China (CHB), and 44 Japanese from Tokyo, Japan (JPT), among which there are 209 unrelated individuals [17, 30]. The Perlegen SNP data set is denser and it contains about 1.6 million SNPs in 71 unrelated individuals from three ancestry populations: 23 African Americans (AA), 24 European Americans (EA) and 24 Han Chinese (HC) from the Los Angeles area [18]. These two large SNP data sets offer high quality and rich density SNP genotypes for the population structure analysis of these ethnic groups. In this study, SNP loci were selected by random sampling from 22 autosomal chromosomes and only unrelated individuals were used.

### AW-clust algorithm

*i*and

*j*was defined as

and *L* is the number of SNP loci used. This, and similar pair-wise distance measures were used by Bowcock et al. [6], Mountain and Cavalli-Sforza [7] and Nakamura et al. [15].

The second stage uses hierarchical clustering to determine ethnic categories. We inferred clusters of individuals from the distance matrix according to Ward's minimum variance algorithm [31, 32]. Here we briefly review the algorithm. In the initial step, each cluster contains one individual. At each step, the algorithm merges the two groups that will result in the smallest increase in the value of within-cluster variance. The pair is then joined and the number of clusters reduced by one. The clustering process continues until one cluster contains all individuals. Therefore, the within-cluster variance takes the minimal increase at each fusion. The cluster variance increases nonlinearly as the clustering process builds up [33], which clearly indicates where groups separate from each other. In this paper, Ward's minimum variance algorithm was implemented with the standard statistical software, R, using the function *hclust* () [34].

### Choice and validation of *K*

We regard the correct number of populations, *K*, as a variable instead of a fixed number that depends on the analysis rather than being an intrinsic biological variable. It depends on the level of population structure that we aim to detect and the number of SNP loci used. For example, we may not be able to separate the CHB and JPT individuals with a small number of random SNP loci but with more markers these two populations are differentiable. The *K* in this paper is identified from the number of major clusters in the hierarchical cluster plot.

Once we determined number of SNP loci needed to differentiate populations, we then confirmed the correct number of populations, *K*, using the gap statistic [16]. If *K* ranges from 1 to *k*, the gap statistic selects the optimal *k* such that log (*W*_{
k
}), where *W*_{
k
}is the pooled within-cluster sum of squares, is farthest below its null reference distribution curve. The gap statistic is defined as *Gap* (*k*) = *E** {log (*W*_{
k
})} - log (*W*_{
k
}), where *E** denotes the expectation from the null reference distribution, in which a uniform distribution was used.

### Clustering quality

A sample was considered correctly assigned if the cluster with the major fraction of ancestry was the same as the ethnic group to which that individual was known to belong [21]. The clustering quality with a given number of SNP loci for each group was measured by Fraction Of Sample (FOS), which is defined as the ratio of the number of individuals of the major group in the cluster (known origin) over all the individuals assigned to the cluster (predicted origin) [10]. We also calculated the Classification Error Rate (CER) for the pooled sample as the proportion of incorrectly assigned individuals in the whole data set. The accuracy of assignment for the pooled sample is defined as 1-CER. Random variation due to SNP sampling was examined by a re-sampling method. SNPs were randomly chosen without replacement from all the SNPs used to re-run the analysis. In each case 100 replicates were performed.

### Simulation study

To evaluate the performance of the clustering algorithm in situations where the classifications are known, we simulated SNP data using the standard coalescent approach [35]. We considered samples of *n* = 50 individuals drawn from two random mating populations, each of size *N* = 10, 000, that had split from a single ancestral population at *t* generations in the past. The mutation rate at each simulated locus was assumed to be negligible. Given the SNP mutation rate is about 10^{-8} per locus per generation [36], this assumption is likely to be valid. Genotypes for *n* individuals from each population were generated by random pairing of 2*n* alleles. We retained only those loci for which polymorphisms remained in the two populations to the current sampling time, *t* = 0.

We estimated the pair-wise distance between individuals from the set of genotypes for the 2*n* simulated individuals. Then we used the Ward's minium variance method to construct a tree from these distances. The quality of separation was evaluated by CER for the 2*n* individuals. For each set of parameters, we performed 100 simulations.

## Declarations

### Acknowledgements

This work was supported in part by NIH grants GM45344 and NS39764 and UNC Genomic Sciences Fellowship. Dr. Bruce Weir provided guidance for this study. We are grateful for Dr. Robert Tibshirani and Amy Kapp's help on the gap statistic. We thank Dr. Dmitri Zaykin and reviewers for helpful comments.

## Authors’ Affiliations

## References

- Lander ES, Schork NJ: Genetic dissection of complex traits. Science. 1994, 265: 2037-2048. 10.1126/science.8091226.View ArticlePubMedGoogle Scholar
- Risch NJ: Searching for genetic determinants in the new millennium. Nature. 2000, 405: 847-856. 10.1038/35015718.View ArticlePubMedGoogle Scholar
- Marchini J, Cardon L, Phillips M, Donnelly P: The effects of human population structure on large genetic association studies. Nat Genet. 2004, 36 (5): 512-517. 10.1038/ng1337.View ArticlePubMedGoogle Scholar
- Freedman M, Reich D, Penney K, McDonald G, Mignault A, Patterson N, Gabriel S, Topol E, Smoller J, Pato C, Pato M, Petryshen T, Kolonel L, Lander E, Sklar P, Henderson B, Hirschhorn J, Altshuler D: Assessing the impact of population stratification on genetic association studies. Nat Genet. 2004, 36: 388-393. 10.1038/ng1333.View ArticlePubMedGoogle Scholar
- Cavalli-Sforza LL, Menozzi P, Piazza A: The history and geography of human genes. Edited by: Princeton, NJ. 1994, Princeton University PressGoogle Scholar
- Bowcock A, Ruiz-Linares A, Tomfohrde J, Minch E, Kidd J, Cavalli-Sforza L: High resolution of human evolutionary trees with polymorphic microsatellites. Nature. 1994, 368: 455-457. 10.1038/368455a0.View ArticlePubMedGoogle Scholar
- Mountain J, Cavalli-Sforza L: Multilocus genotypes, a tree of individuals, and human evolutionary history. Am J Hum Genet. 1997, 61: 705-718.PubMed CentralView ArticlePubMedGoogle Scholar
- Rosenberg N, Pritchard J, Weber J, Cann H, Kidd K, Zhivotovsky L, Feldman M: Genetic structure of human populations. Science. 2002, 298: 2381-2385. 10.1126/science.1078311.View ArticlePubMedGoogle Scholar
- Shriver M, Kennedy G, Parra E, Lawson H, Sonpar V, Huang J, Akey J, Jones K: The genomic distribution of population substructure in four populations using 8,525 autosomal SNPs. Hum Genomics. 2004, 1: 274-286.PubMed CentralView ArticlePubMedGoogle Scholar
- Turakulov R, Easteal S: Number of SNPs loci needed to detect population structure. Hum Hered. 2003, 55: 37-45. 10.1159/000071808.View ArticlePubMedGoogle Scholar
- Pritchard JK, Stephens M, Donelly P: Inference of population structure using multilocus genotype data. Genetics. 2000, 155 (2): 945-959. 10.1086/302959.PubMed CentralPubMedGoogle Scholar
- Yang BZ, Zhao H, Kranzler HR, Gelernter J: Practical population group assignment with selected informative markers: Characteristics and properties of Bayesian clustering via STRUCTURE. Genet Epidemiol. 2005, 28: 302-312. 10.1002/gepi.20070.View ArticlePubMedGoogle Scholar
- Purcell S, Sham P: Properties of structured association approaches to detecting population stratification. Hum Hered. 2004, 58: 93-107. 10.1159/000083030.View ArticlePubMedGoogle Scholar
- Falush D, Stephens M, Pritchard J: Inference of population structure using multilocus genotype data: Linked loci and correlated allele frequencies. Genetics. 2003, 164: 1567-1587.PubMed CentralPubMedGoogle Scholar
- Nakamura T, Shoji A, Fujisawa H, Kamatani N: Cluster analysis and association study of structured multilocus genotype data. J Hum Genet. 2005, 50: 53-61. 10.1007/s10038-004-0220-x.View ArticlePubMedGoogle Scholar
- Tibshirani R, Walther G, Hastie T: Estimating the number of clusters in a data set via the gap statistic. J R Statist Soc B. 2001, 63: 411-423. 10.1111/1467-9868.00293.View ArticleGoogle Scholar
- The international HapMap consortium: A haplotype map of the human genome. Nature. 2005, 437: 1299-1320. 10.1038/nature04226.PubMed CentralView ArticleGoogle Scholar
- Hinds D, Stuve L, Nilsen G, Halperin E, Eskin E, Ballinger D, Frazer K, Cox D: Whole genome patterns of common DNA variation in three human populations. Science. 2005, 307: 1072-1079. 10.1126/science.1105436.View ArticlePubMedGoogle Scholar
- Reed E: Number of gene loci required for accurate estimation of ancestral population proportions in individual human hybrids. Nature. 1973, 244: 575-576. 10.1038/244575a0.View ArticlePubMedGoogle Scholar
- Rosenberg NA, Li LM, Ward R, Pritchard JK: Informativeness of genetic markers for inference of ancestry. Am J Hum Genet. 2003, 73: 1402-1422. 10.1086/380416.PubMed CentralView ArticlePubMedGoogle Scholar
- Bamshad M, Wooding S, Watkins W, Ostler C, Batzer M, Jorde L: Human population genetic structure and inference of group membership. Am J Hum Genet. 2003, 72: 578-589. 10.1086/368061.PubMed CentralView ArticlePubMedGoogle Scholar
- Weir BS, Cardon LR, Anderson AD, Nielsen DM, Hill WG: Measures of human population structure show heterogeneity among genomic regions. Genome Res. 2005, 15: 1468-1476. 10.1101/gr.4398405.PubMed CentralView ArticlePubMedGoogle Scholar
- Balding DJ, Nichols RA: DNA profile match probability calculation: how to allow for population stratification, relatedness, database selection and single bands. Forensic Sci Int. 1994, 64: 125-140. 10.1016/0379-0738(94)90222-4.View ArticlePubMedGoogle Scholar
- Gao X: Using allele sharing distance for detecting human population stratification. Unpublished.Google Scholar
- Anderberg MR: Cluster Analysis for Applications. 1973, New York: Academic PressGoogle Scholar
- Borg I, Groenen PJF: Modern multidimensional scaling: theory and applications. 1997, Springer-Verlag, BerlinView ArticleGoogle Scholar
- McVean G, Spencer CCA, Chaix R: Perspectives on human genetic variation from the HapMap project. PLoS Genetics. 2005, 1: e54-10.1371/journal.pgen.0010054.PubMed CentralView ArticlePubMedGoogle Scholar
- Rosenberg NA, Mahajan S, Ramachandran S, Zhao C, Pritchard JK, Feldman MW: Clines, clusters, and the effect of study design on the inference of human population structure. PLoS Genetics. 2005, 1: e70-10.1371/journal.pgen.0010070.PubMed CentralView ArticlePubMedGoogle Scholar
- Yang Bz, Zhao H, Kranzler HR, Gelernter J: Characterization of a likelihood based method and effects of markers informativeness in evaluation of admixture and population group assignment. BMC Genet. 2005, 6: 50-10.1186/1471-2156-6-50.PubMed CentralView ArticlePubMedGoogle Scholar
- The international HapMap consortium: The international HapMap project. Nature. 2003, 426: 789-796. 10.1038/nature02168.View ArticleGoogle Scholar
- Ward JH: Hierarchical grouping to optimize an objective function. J Ame Stat Assoc. 1963, 58: 236-244. 10.2307/2282967.View ArticleGoogle Scholar
- Ward JH, Hook ME: Application of an hierarchical grouping procedure to a problem of grouping profiles. Educ and Phsychol Measurement. 1963, 23: 69-81. 10.1177/001316446302300107.View ArticleGoogle Scholar
- Romesburg CH: Cluster analysis for researchers. 1984, Wadsworth, IncGoogle Scholar
- Team RDC: R: A language and environment for statistical computing. 2007, R Foundation for Statistical ComputingGoogle Scholar
- Hudson RR: Gene genealogies and the coalescent process. 1990, Oxford University Press, Oxford, oxford surveys in evolutionary biology edition, 7:Google Scholar
- Kruglyak L, Nickerson DA: Variation is the spice of life. Nat Genet. 2001, 27: 234-236. 10.1038/85776.View ArticlePubMedGoogle Scholar

## Copyright

This article is published under license to BioMed Central Ltd. This is an Open Access article distributed under the terms of the Creative Commons Attribution License (http://creativecommons.org/licenses/by/2.0), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.