 Methodology article
 Open access
 Published:
Determination of sample size for a multiclass classifier based on singlenucleotide polymorphisms: a volume under the surface approach
BMC Bioinformatics volume 15, Article number: 190 (2014)
Abstract
Background
Data on singlenucleotide polymorphisms (SNPs) have been found to be useful in predicting phenotypes ranging from an individual’s class membership to his/her risk of developing a disease. In multiclass classification scenarios, clinical samples are often limited due to cost constraints, making it necessary to determine the sample size needed to build an accurate classifier based on SNPs. The performance of such classifiers can be assessed using the Area Under the Receiver Operating Characteristic (ROC) Curve (AUC) for two classes and the Volume Under the ROC hyperSurface (VUS) for three or more classes. Sample size determination based on AUC or VUS would not only guarantee an overall correct classification rate, but also make studies more costeffective.
Results
For coded SNP data from D(≥2) classes, we derive an optimal Bayes classifier and a linear classifier, and obtain a normal approximation to the probability of correct classification for each classifier. These approximations are then used to evaluate the associated AUCs or VUSs, whose accuracies are validated using Monte Carlo simulations. We give a sample size determination method, which ensures that the difference between the two approximate AUCs (or VUSs) is below a prespecified threshold. The performance of our sample size determination method is then illustrated via simulations. For the HapMap data with three and four populations, a linear classifier is built using 92 independent SNPs and the required total sample sizes are determined for a continuum of threshold values. In all, four different sample size determination studies are conducted with the HapMap data, covering cases involving wellseparated populations to poorlyseparated ones.
Conclusion
For multiclasses, we have developed a sample size determination methodology and illustrated its usefulness in obtaining a required sample size from the estimated learning curve. For classification scenarios, this methodology will help scientists determine whether a sample at hand is adequate or more samples are required to achieve a prespecified accuracy. A PDF manual for R package “SampleSizeSNP” is given in Additional file 1, and a ZIP file of the R package “SampleSizeSNP” is given in Additional file 2.
Background
Data on singlenucleotide polymorphisms (SNPs) have been found to be useful in predicting an individual’s class membership or his/her response to a drug, susceptibility to environmental factors such as toxins, and the risk of developing a particular disease, among others [1–5]. The classification literature provides a variety of classifiers (e.g., Support Vector Machine, genetic programming, Neural Networks and Logistic Regression) and sample size determination methods [6–10], but most of these are only applicable to continuous data.
Recently Liu et al. [11] developed an optimal Bayes classifier and a linear classifier for coded SNP data from two classes, and obtained a normal approximation to the probability of correct classification (PCC) for each classifier. They also proposed a sample size determination methodology to determine an adequate sample size, which ensures that the difference between the two approximate PCCs is below a prespecified threshold value. Using Monte Carlo simulations, Liu et al. [11] assessed the validity of their approximations. Furthermore, they illustrated the performance of their sample size determination method via simulations and a real data analysis using the HapMap data on two populations—Chinese and Japanese.
While Liu et al. [11] showed that their sample size determination method is competitive, they also pointed out that an additional maximization step is required in order to determine the discrimination values for each of their classifiers; see their REMARK1 in their article for more details. When there are three or more classes, however, determination of such discrimination values is not only more difficult, but also increases the overall computational burden. In a twoclass scenario, a well known way to overcome this difficulty is to consider the Receiver Operating Characteristic (ROC) curve, which plots the True Positive Rates vs. False Positives Rates, at various discrimination values [12, 13]. Note that the ROC allows the discrimination value to be varied and it simultaneously explores all possible combinations of the correct classification rates [14]. The Area Under the ROC curve (AUC) is commonly used as a scalar performance measure, which allows classifiers to be compared independent of the discrimination values. Unfortunately, the AUC measure is only applicable to a twoclass scenario. A popular extension of the AUC measure, known as the Volume Under the ROC hyperSurface (VUS) measure, is often used in a multiclass scenario (see e.g., Landgrebe and Duin [14] and Landgrebe and Paclik 2010 [15]).
This article revisits the problem of sample size determination in classification scenarios involving coded SNP data, but uses the AUC and the VUS as performance measures for twoclass and multiclass scenarios, respectively. More specifically, for coded SNP data from D(≥2) classes, we derive an optimal Bayes classifier and obtain a normal approximation to its probability of correct classification, which is denoted by P C C(∞). We also derive a linear classifier and obtain a normal approximation to its probability of correct classification, which is denoted by \mathit{\text{PCC}}\left(\overrightarrow{n}\right). For an overall assessment of each of the classifiers, we define the scalar measures AUC (for twoclass) and VUS (for multiclass), and correspondingly define the quantities \mathit{\text{AUC}}\left(\infty \right),\mathit{\text{AUC}}\left(\overrightarrow{n}\right),\mathit{\text{VUS}}\left(\infty \right)\phantom{\rule{1em}{0ex}}\text{and}\phantom{\rule{1em}{0ex}}\mathit{\text{VUS}}\left(\overrightarrow{n}\right) for each classification scenario. For the twoclass scenario, we propose to determine the sample size n for which \mathit{\text{AUC}}\left(\infty \right)\mathit{\text{AUC}}\left(\overrightarrow{n}\right)<\gamma, where γ∈(0,1) is a prespecified threshold value. Whereas, for the multiclass scenario, we propose to determine the sample size n for which \mathit{\text{VUS}}\left(\infty \right)\mathit{\text{VUS}}\left(\overrightarrow{n}\right)<\gamma. A computational method to determine the total sample size for various values of γ is described. Monte Carlo simulations are carried out to corroborate our theoretical approximations, and the performance of our sample size determination method is assessed via simulations and analysis of the HapMap data consisting of 3 and 4 populations, respectively. In all, four different sample size determination studies are conducted with the HapMap data, covering cases involving wellseparated populations to poorlyseparated ones. Details are given in the data analysis section.
R software was used to carry out all the computations. A PDF manual for R package “SampleSizeSNP” is given in Additional file 1, and a ZIP file of the R package “SampleSizeSNP” is given in Additional file 2.
Methods
Assumptions
Suppose there are D(≥2) distinct classes denoted by C_{1},…,C_{ D }, consisting of n_{1},…,n_{ D } subjects, respectively. For each subject, we observe a pdimensional SNP vector, \overrightarrow{x}={({x}_{1},{x}_{2},\mathrm{..},{x}_{p})}^{\prime}, where typically p is much larger (>>) than \sum _{i=1}^{D}{n}_{i}, and the jth SNP is coded in such a way x_{ j }=0,1,2, which denotes the number of minor alleles in the genotype “aa”, “Aa” and “AA”, respectively. It is possible that some of the SNPs are highly correlated, leading us to choose one SNP to represent a set of highly correlated ones. For classification and sample size determination, we make the following assumptions:

1.
For an m such that \sum _{i=1}^{D}{n}_{i}<<m<p, the data vector \overrightarrow{x}={({x}_{1},\dots ,{x}_{m})}^{\prime} consists only of m SNPs, which are statistically independent. That is, the rest of the (p−m) correlated SNPs are not used for classification.

2.
For each k=1,…,D and j=1,…,m, we postulate HardyWeinberg equilibrium, according to which the probability mass function of the coded SNP (X _{ j }) belonging to class k is given by
\begin{array}{l}{P}_{k}({X}_{j}={x}_{j}{\theta}_{k,j})=\left(\genfrac{}{}{0ex}{}{2}{{x}_{j}}\right){\theta}_{k,j}^{{x}_{j}}{(1{\theta}_{k,j})}^{2{x}_{j}},\phantom{\rule{1em}{0ex}}\phantom{\rule{1em}{0ex}}{x}_{j}=0,1,2,\end{array}where θ_{k,j} is the minor allele frequency at locus j in class k, and by definition θ_{k,j}∈(0.01,0.5). Here, θ_{k,j}<0.5 because it is the minor allele frequency, and θ_{k,j}>0.01 ensures that the polymorphism is not a mutation. For each k=1,…,D, let {\overrightarrow{\theta}}_{k}={({\theta}_{k,1},\dots ,{\theta}_{k,m})}^{\prime} denote the parameter vector corresponding to the class C_{ k }.

3.
There is a percentage ρ of the m SNPs with marginal effect on any two classes, and let l=⌊ρ m⌋ be the number of SNPs with marginal effects.
The optimal classifier and its PCC
By the assumptions above, the conditional mass function of \overrightarrow{X}={({X}_{1},\dots ,{X}_{l})}^{\prime} given the class C_{ k }, k=1,…,D, is
Suppose {\pi}_{k}=P(\overrightarrow{x}\in {C}_{k}) and we denote the marginal mass function f\left(\overrightarrow{x}\right)=\sum _{k=1}^{D}{\pi}_{k}{f}_{k}\left(\overrightarrow{x}\right{\overrightarrow{\theta}}_{k}), then for each 1≤k≤D, the posterior mass function of the class C_{ k } given \overrightarrow{x} is
For any fixed k=1,…,D, the Bayes classification rule then classifies \overrightarrow{x} to the class C_{ k } if
for all k^{′}≠k. This leads to the optimal Bayes classifier, which classifies \overrightarrow{x} to C_{ k } if
for all k^{′}≠k, where
Then, the PCC of the optimal Bayes classifier is defined as
In Additional file 3: Appendix 1, we derive a normal approximation for P C C(∞), as l→∞. That is, for large l, we show that
where ϕ is the (D−1)dimensional multivariate normal density, \underset{{\overrightarrow{\mathbf{K}}}_{k}}{\overset{\infty}{\int}} is a multiple integral, {\overrightarrow{\mathbf{K}}}_{k} and {\overrightarrow{\mathit{\mu}}}_{l,k} are (D−1)×1 vectors, and Σ_{l,k} is a (D−1)×(D−1) matrix. All these quantities are defined in Additional file 3: Appendix 1.
In Additional file 3: Appendix 4, we give an expression for (4) for the case D=3.
A linear classifier and its PCC
Motivated by the form of the optimal Bayes classifier in (2), we consider the following linear classifier that classifies \overrightarrow{x} to the class C_{ k } if
for all k^{′}≠k, where {\widehat{b}}_{k,{k}^{\prime}}^{j}=log\left(\frac{{\widehat{\theta}}_{k,j}(1{\widehat{\theta}}_{{k}^{\prime},j})}{{\widehat{\theta}}_{{k}^{\prime},j}(1{\widehat{\theta}}_{k,j})}\right), {\widehat{\theta}}_{k,j}\phantom{\rule{1em}{0ex}}\text{and}\phantom{\rule{1em}{0ex}}{\widehat{\theta}}_{{k}^{\prime},j} are the maximum likelihood estimators of {\theta}_{k,j}\phantom{\rule{1em}{0ex}}\text{and}\phantom{\rule{1em}{0ex}}{\theta}_{{k}^{\prime},j}, respectively. Also, the values of the weights w_{j,n}(k,k^{′}) in (5) are determined in the following way: For each j=1,…,m and k^{′}≠k, suppose we test the hypothesis {H}_{0,j}^{k,{k}^{\prime}}:{\theta}_{k,j}={\theta}_{{k}^{\prime},j} versus {H}_{1,j}^{k,{k}^{\prime}}:{\theta}_{k,j}\ne {\theta}_{{k}^{\prime},j}. Then w_{j,n}(k,k^{′})=1 if {H}_{0,j}^{k,{k}^{\prime}} is rejected; else w_{j,n}(k,k^{′})=0. In Additional file 3: Appendix 2, we use the large sample theory to derive a Wald test of level α to test {H}_{0,j}^{k,{k}^{\prime}} versus {H}_{1,j}^{k,{k}^{\prime}}, and an expression for the power, 1{\beta}_{j}^{k,{k}^{\prime}}({n}_{k},{n}_{{k}^{\prime}},{h}_{j}), of this test, when {\theta}_{k,j}{\theta}_{{k}^{\prime},j}={h}_{j}.
In Additional file 3: Appendix 3, we derive a normal approximation for the PCC of the linear classifier, denoted by \mathit{\text{PCC}}\left(\overrightarrow{n}\right). That is, for large l, we show that
Note that \mathit{\text{PCC}}\left(\overrightarrow{n}\right) depends on \overrightarrow{n}={({n}_{1},\dots ,{n}_{D})}^{\prime} through ({\stackrel{~}{\overrightarrow{\mathit{\mu}}}}_{m,k},{\stackrel{~}{\mathit{\Sigma}}}_{m,k}); see Additional file 3: Appendix 3 for details. In Additional file 3: Appendix 4, we give an expression for (6) for the case D=3.
AUC and VUSfor the optimal and linear classifiers
For any (k,k^{′}), define
Then, for the optimal Bayes classifier in (2) we have from (4) that
and similarly, for the linear classifier in (5), we have from (6) that
for k=1,…,D. When D=2, for the optimal Bayes classifier, the R O C(∞) for two classes is the curve ξ_{2,2} vs. (1−ξ_{1,1}). Then, the A U C(∞) is
However, when the number of classes D≥3, we need to consider the volume under the ROC hypersurface. Following the work of Landgrebe and Duin [14], the VUS is defined as
By replacing ξ_{k.k} by {\stackrel{~}{\xi}}_{k,k} [see (8)] in the above definitions of R O C,A U C and the VUS, we obtain corresponding expressions for the linear classifier in (5). We denote the resulting ones as \mathit{\text{AUC}}\left(\overrightarrow{n}\right) and \mathit{\text{VUS}}\left(\overrightarrow{n}\right). In Additional file 3: Appendix 4, we derive these expressions for the case D=3.
Computation of VUS
As is evident from (9), the computation of VUS involves high dimensional integration. Given below is a brief description of the steps involved in the computation of VUS. For ease of exposition, we will denote ξ_{ k }=ξ_{k,k}, k=1,…,D. First, we randomly generate the thresholds \overrightarrow{K}=({K}_{1},{K}_{2},\dots ,{K}_{D1}) (see (9)) and compute the corresponding \overrightarrow{\xi}={({\xi}_{1},{\xi}_{2},\dots ,{\xi}_{D})}^{\prime} satisfying (7). Note that the \overrightarrow{\xi} contributes to the integration in VUS only if all the ξ_{ k }’s are positive.
To find as many \overrightarrow{\xi} values that contribute to the integration as possible, we use the ant colony optimization algorithm, where only the \overrightarrow{K} values corresponding to the \overrightarrow{\xi} values that contribute to the integration are retained. However, these are perturbed by a small noise and the resulting \overrightarrow{K} values are used as seeds for the next iteration. Then, we use the genetic algorithm to obtain another \overrightarrow{\xi} value located in a different region within (0,1)^{k}, which also contributes to the integration. We use the ant colony algorithm and the genetic algorithm alternatively to eventually generate a dense set of \overrightarrow{\xi}\phantom{\rule{1em}{0ex}}(\in {(0,1)}^{k}) values that contribute to the integration. Note that the process is such that the newly generated \overrightarrow{\xi} values are appended to all the previously generated \overrightarrow{\xi} values.
Now, to compute the volume, V U S(∞), we use the convhulln function in the qhull Rpackage. Note that the convhulln function is designed to determine the convex hull of a set of Ddimensional points and thus compute the volume of the hull. In view of this, in order to compute the volume, V U S(∞), a base of \overrightarrow{\xi} (this is same as the \overrightarrow{\xi} vector, except that one of its components, e.g. the first component, is set to 0) is appended to the original \overrightarrow{\xi}. Since in each iteration the new \overrightarrow{\xi} values are appended to the old \overrightarrow{\xi} values from the previous iterations, and the VUS is concave, the computed VUS is supposed to increase in value with each iteration. We stop appending the new \overrightarrow{\xi} values when V U S_{ o l d }−V U S_{ n e w }<0.001. When this criterion is satisfied, we obtain the value of V U S(∞). Similarly, the values of \mathit{\text{AUC}}\left(\infty \right),\mathit{\text{AUC}}\left(\overrightarrow{n}\right),\phantom{\rule{1em}{0ex}}\text{and}\phantom{\rule{1em}{0ex}}\mathit{\text{VUS}}\left(\overrightarrow{n}\right) are calculated.
Sample size determination using VUS or AUC
Given a threshold γ, we determine the sample size n satisfying the following condition:
For the case D=2, we determine the sample size n satisfying the condition: \mathit{\text{AUC}}\left(\infty \right)\mathit{\text{AUC}}\left(\overrightarrow{n}\right)<\gamma. A simulation study for the case D=2 is carried out in Additional file 3: Appendix 5 to assess the performance of our sample size determination algorithm.
Results
Monte Carlo simulations
Before we illustrate the performance of our sample size determination method based on AUC or VUS, we present results from an extensive Monte Carlo simulation study conducted to verify the accuracy of the approximations for \mathit{\text{AUC}}\left(\overrightarrow{n}\right) and \mathit{\text{VUS}}\left(\overrightarrow{n}\right), respectively, and study their behavior as a function of n and other parameters. Here, we present the numerical assessments based on the VUS for the cases D=3 and 4, respectively. However, as mentioned above, the assessments based on the AUC for the case D=2 are given in Additional file 3: Appendix 5. Henceforth, we will set n_{ k }=n for all k=1,…,D, and we will use n instead of \overrightarrow{n} to simplify notations.
When D=3, we consider the following simulation set up: For {\overrightarrow{\theta}}_{1}={({\theta}_{1,1},\dots ,{\theta}_{1,m})}^{\prime}, let θ_{1,j}∼U(0.4,0.49), j=1,…,m; for a specified scalar value h, let {\overrightarrow{h}}_{1},{\overrightarrow{h}}_{2} be such that their components h_{i,j}∼U(h−0.002,h+0.002), i=1,2; j=1,…,m; and let {\overrightarrow{\theta}}_{2}={\overrightarrow{\theta}}_{1}{\overrightarrow{h}}_{1}, {\overrightarrow{\theta}}_{3}={\overrightarrow{\theta}}_{2}{\overrightarrow{h}}_{2}. First, we generated a ({\overrightarrow{\theta}}_{1},{\overrightarrow{\theta}}_{2},{\overrightarrow{\theta}}_{3}) according to the above set up, and then generated the data vector \overrightarrow{x}={({x}_{1},\dots ,{x}_{m})}^{\prime} for each class. We then computed \widehat{\mathit{\text{VUS}}\left(\infty \right)} and \widehat{\mathit{\text{VUS}}\left(n\right)} following the computational methodology described earlier. For this ({\overrightarrow{\theta}}_{1},{\overrightarrow{\theta}}_{2},{\overrightarrow{\theta}}_{3}), we then drew twenty \overrightarrow{x} data sets and calculated a Monte Carlo estimate, denoted by \widehat{\mathit{\text{VUS}}\left(n\right)}\text{MC}. This process was repeated 20 times and an average value of \widehat{\mathit{\text{VUS}}\left(n\right)}\text{MC} was computed. These are given in Table 1. It is evident from Table 1 that the \widehat{\mathit{\text{Bias}}}=\widehat{\mathit{\text{VUS}}\left(n\right)}\text{MC}\widehat{\mathit{\text{VUS}}\left(n\right)} is negligible in most cases, which validates the use of our approximation for V U S(n). Table 1 also gives similar results for the case D=4. Note that V U S(∞)=1/D! for a random classifier, which is the lower bound of V U S(∞) for any classifier.
Next, we determine the smallest n such that f\left(n\right)=\widehat{\mathit{\text{VUS}}\left(\infty \right)}\widehat{\mathit{\text{VUS}}\left(n\right)}\gamma <0, for a prespecified γ value. We use the following algorithm to determine such an n: (i) Let n=n_{ S } and n_{ L } such that f(n_{ S })>0 and f(n_{ L })<0, and set n_{ M }=[(n_{ S }+n_{ L })/2]. The algorithm begins by selecting a small n_{ S } and a large n_{ L }; (ii) If f(n_{ M })f(n_{ S })<0, then reset n_{ L }=n_{ M }; or else, reset n_{ S }=n_{ M }. In either case, return to step (i), unless n_{ L }−n_{ S }≤1, in which case, the smallest sample n=n_{ L }; (iii) Use the smallest (total) sample of size D×n_{ L }, with n=n_{ L } from each class, C_{1},…,C_{ D }. We implemented this algorithm for each value of h, m and significance level α for the Wald test; see discussion below (5). For the cases D=2 and D=3, respectively, Table 2 displays the determined sample sizes for γ=0.01 and each combination of parameter values. From Table 2, it is evident that the required sample size reduces as h increases, as expected. Hence, f(n)<0 for smaller sample sizes, as shown in Table 2. However, the effect of m on the determined sample sizes is less clear. When h is large, say h≥0.1, then the required sample size reduces as m becomes large. Whereas, when h is small, say h=0.05, the reverse is true as m becomes large.
Application to the HapMap data
The aim of the International HapMap Project is to develop a haplotype map of the human genome, which will describe the common patterns of human DNA sequence variation.
The HapMap data (Phase III) consists of eleven populations with about p=1.2×10^{6} SNPs. Here, we consider the following nine populations in order to illustrate our sample size determination algorithm: ASW—African ancestry in Southwest USA with 87 subjects; CEU—Utah residents with Northern and Western European ancestry from CEPH collection with 167 subjects; CHB—the Han Chinese individuals from Beijing with 137 subjects; CHD—Chinese in Metropolitan Denver, Colorado with 109 subjects; GIH—Gujarati Indians in Houston, Texas with 101 subjects; JPT—the Japanese individuals from Tokyo with 113 subjects; MEX—Mexican ancestry in Los Angeles, California with 86 subjects; TSI—Toscans in Italy (TSI) with 102 subjects; and YRI—Yoruba in Ibadan, Nigeria with 203 subjects. With these, we created four sample size determination studies, of which the first three involve three populations (D=3), and the last study involves four populations (D=4). More specifically, we conducted our sample size determination studies with the following population groupings: (I) (CEU, GIH, MEX); (II) (ASW, TSI, YRI); (III) (CHB, JPT, CHD); and (IV) (CHB, JPT, CHD, GIH).
Based on all the available subjects, we extracted pairwise independent SNPs using the following steps. Suppose L is a set of SNPs, then: (I) form a set S with one SNP from L and update S after the next step; (II) from the remaining SNPs in L, choose one SNP that is independent of every SNP in S using Kendall’s τ coefficient as a test statistic to test pairwise independence, and then add this new SNP to S. Here, we concluded independence if the Kendall’s τvalue <0.05; (III) Repeat (II) until each remaining SNP in L is correlated with at least one SNP in S. This procedure yielded a set S with m=92 pairwise independent SNPs, and with these we built our linear classifier.
Next, we set ρ=1 so that m=l=92; see Assumption 3 under the Methods section. Recall that \overrightarrow{{\theta}_{k}}={({\theta}_{k,1},\dots ,{\theta}_{k,l})}^{\prime} for k=1,…,D. For the cases D=3 and D=4 considered in studies (I) to (IV) above, we estimated \overrightarrow{{\theta}_{k}} using the maximum likelihood (ML) estimates obtained based on all the available subjects belonging to the respective populations. We then substituted these ML estimates into the corresponding expressions for \widehat{\mathit{\text{VUS}}\left(\infty \right)} and \widehat{\mathit{\text{VUS}}\left(n\right)}, respectively. Figures 1, 2 and 3 show plots of required sample sizes for a continuum of threshold values γ for the case D=3 considered in studies (I) to (III), respectively, and Figure 4 plots the same for D=4 considered in study (IV). From these figures, the required total sample size can be determined approximately for each prespecified γ value.
For example, if we set γ=0.10 (i.e., \widehat{\mathit{\text{VUS}}\left(\infty \right)}\widehat{\mathit{\text{VU}}}S\left(n\right)<0.10), then in the three population (CEU,GIH, MEX) case, the \widehat{\mathit{\text{VUS}}\left(\infty \right)}=0.9046 and about 62 observations are required for each class with a total sample size of 186, whereas in the three population (ASW, TSI, YRI) case, the \widehat{\mathit{\text{VUS}}\left(\infty \right)}=0.7557 and about 150 observations are required for each class with a total sample size of 450. Note that, for γ=0.10, in study (I) the required sample sizes for each population is less than what is currently available, whereas in study (II), we would need 63 and 48 more observations for the populations ASW and TSI, respectively. For the three population (CHB, JPT and CHD) case, if we set γ=0.10 then the \widehat{\mathit{\text{VUS}}\left(\infty \right)}=0.6178 and about 244 observations are required for each class with a total sample size of 732. Clearly, for study (III) at least 100 more observations are needed for each population (CHB, JPT and CHD) when γ=0.10. Finally, for the four population (CHB, JPT, CHD, GIH) case, setting γ=0.10 yields that the \widehat{\mathit{\text{VUS}}\left(\infty \right)}=0.5580 and about 279 samples are required for each class with a total sample of 1,116. Once again, at least 150 more observations are needed for each of the four populations when γ=0.10.
The results from the four HapMap studies suggest that the \widehat{\mathit{\text{VUS}}\left(\infty \right)} value is large and the required total sample size is small when the populations are wellseparated [as in study (I)]. Whereas, when the populations are moderatelyseparated [as in study (II), where the populations ASW and YRI may be similar], the \widehat{\mathit{\text{VUS}}\left(\infty \right)} value reduces and the required total sample size increases moderately. When the populations are poorlyseparated [as in study (III), where all the three populations may be similar], the \widehat{\mathit{\text{VUS}}\left(\infty \right)} value reduces even further and there is a substantial increase in the required total sample size. Finally, in the four population study, where three of the populations are poorlyseparated, once again we see a further reduction in the \widehat{\mathit{\text{VUS}}\left(\infty \right)} value and a corresponding increase in the required total sample size. Although not reported here, we also considered other well/moderate/poorly separated cases with the HapMap data and observed similar results as the ones reported here.
It is well known in the classification literature that the performance of a classifier depends on how well separated the classes are. Similarly, the studies above involving the HapMap data show that the performance of our sample size determination methodology also depends on the extent of separation between populations. While our methodology provides a formal way of determining an approximate total sample size for each specified value of γ, it is clear from the HapMap data analysis that it is not possible to propose a universal γ value. Nevertheless, if the classes are wellseparated or moderatelyseparated, then we believe that γ=0.10 may be a good choice for many frequently encountered data sets in classification problems.
Discussion
We have built an optimal Bayes classifier and a linear classifier based on coded SNP data from two or more classes. For these classifiers, we have considered the two commonly used scalar performance measures, the Area Under the ROC curve (AUC) and the Volume Under the ROC hyperSurface (VUS), which allow classifiers to be compared independent of discrimination values. We have illustrated the performance of a sample size determination methodology, which selects the smallest total sample size n such that the criterion \widehat{\mathit{\text{VUS}}\left(\infty \right)}\widehat{\mathit{\text{VUS}}\left(n\right)}<\gamma is satisfied. While the approximations to the VUS (or AUC) obtained here provide the necessary theoretical justification, the simulations and the HapMap data analysis presented here illustrate the practical value of our sample size determination method.
The fact that the HapMap contains data on multiple populations belonging to similar or dissimilar geographical locations enabled us to test the performance of our sample size determination method on three different multiclass scenarios involving wellseparated, moderatelyseparated, and poorlyseparated populations. We have shown that the the extent of separation between the populations and the choice of threshold value affect the total sample size required to satisfy the criterion. With regard to the choice of the threshold value γ in other practical contexts, we recommend that the user take into consideration the cost of obtaining more samples and choose an appropriate value of γ that gives an acceptable precision. In other words, if the cost of sampling is affordable then the user may want to sample more to achieve a higher precision (lower γ value) using our classifier; otherwise, the user has to settle for a higher γ value that makes use of all the available samples. We also infer from our HapMap data analysis that a value of \widehat{\mathit{\text{VUS}}\left(\infty \right)}>0.80 may indicate the extent of separation between the classes. Thus, the value of \widehat{\mathit{\text{VUS}}\left(\infty \right)} could also give some prior guidance on the choice of γ values, especially in instances where the cost of sampling is a serious concern.
Conclusion
In summary, for multiple classes, we have developed an asymptotic methodology based on AUC or VUS to estimate the learning curve of SNP classifiers. It is shown that the required total sample size can be obtained from the estimated learning curve for each prespecified threshold value. In classification problems, sample size determination is important due to cost considerations. This methodology will help scientists determine if a sample at hand is adequate or more observations are necessary to achieve a prespecified accuracy, and thus help users strike an optimal balance between precision and cost.
References
Guzzetta G, Jurman G, Furlanello C: A machine learning pipeline for quantitative phenotype prediction from genotype data. BMC Bioinformatics. 2010, 11 (Suppl 8): S310.1186/1471210511S8S3.
Lee SH, van der Werf JHJ, Hayes BJ, Goddard ME, Visscher PM: Predicting unobserved phenotypes for complex traits from wholegenome SNP data. Plos Genet. 2008, 4: e100023110.1371/journal.pgen.1000231.
Nunkesser R, Bernholt T, Schwender H, Ickstadt K, Wegener I: Detecting highorder interactions of single nucleotide polymorphisms using genetic programming. Bioinformatics. 2007, 23: 32803288. 10.1093/bioinformatics/btm522.
Wray NR, Goddard ME, Visscher PM: Prediction of individual genetic risk to disease from genomewide association studies. Genome Res. 2007, 17: 15201528. 10.1101/gr.6665407.
Zhou N, Wang L: Effective selection of informative SNPs and classification on the HapMap genotype data. BMC Bioinformatics. 2007, 8: 484492. 10.1186/147121058484.
De Valpine P, Bitter HM, Brown MPS, Heller J: A simulationapproximation approach to sample size planning for highdimensional classification studies. Biostatistics. 2009, 10: 424435. 10.1093/biostatistics/kxp001.
Dobbin KK, Simon RM: Sample size determination in microarray experiments for class comparison and prognostic classification. Biostatistics. 2005, 6: 2738. 10.1093/biostatistics/kxh015.
Dobbin KK, Simon RM: Sample size planning for developing classifiers using highdimensional DNA microarray data. Biostatistics. 2007, 8: 101117. 10.1093/biostatistics/kxj036.
Dobbin KK, Zhao Y, Simon RM: How large a training set is needed to develop a classifier for microarray data. Clin Cancer Res. 2008, 14: 108114. 10.1158/10780432.CCR070443.
Mukherjee S, Tamayo P, Rogers S, Rifkin R, Engle A, Campbell C, Golub TR, Mesirov JP: Estimating dataset size requirements for classifying DNA microarray data. J Comput Biol. 2003, 10: 119142. 10.1089/106652703321825928.
Liu X, Wang Y, Rekhaya R, Sriram TN: Sample size determination for classifiers based on singlenucleotide polymorphisms. Biostatistics. 2012, 13: 217227. 10.1093/biostatistics/kxr053.
Metz C: Basic principles of ROC analysis. Seminars Nucl Med. 1978, 3: 283298.
Fawcett T: An introduction to ROC analysis. Pattern Recogn Lett. 2005, 27: 861874.
Landgrebe T, Duin RPW: Approximating the multiclass ROC by pairwise analysis. Pattern Recogn Lett. 2007, 28: 17471758. 10.1016/j.patrec.2007.05.001.
Landgrebe T, Paclik P: The ROC skeleton for multiclass ROC estimation. Pattern Recogn Lett. 2010, 31: 949958. 10.1016/j.patrec.2009.12.037.
Acknowledgements
We would like to thank the Editor and the two reviewers for their careful reading and insightful suggestions, which greatly improved the content and the presentation of the article. T.N.S. was supported by a grant from the National Security Agency [H982301110188] and the National Science Foundation [#1309665].
Author information
Authors and Affiliations
Corresponding author
Additional information
Competing interests
The authors declare that they have no competing interests.
Authors’ contributions
XL developed and implemented the proposed model, performed simulation and application, and drafted the manuscript. TNS participated in model development and helped manuscript preparation. YW participated in HapMap data analysis. All authors read and approved the final manuscript.
Authors’ original submitted files for images
Below are the links to the authors’ original submitted files for images.
Rights and permissions
Open Access This article is published under license to BioMed Central Ltd. This is an Open Access article is distributed under the terms of the Creative Commons Attribution License ( https://creativecommons.org/licenses/by/2.0 ), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.
About this article
Cite this article
Liu, X., Wang, Y. & Sriram, T. Determination of sample size for a multiclass classifier based on singlenucleotide polymorphisms: a volume under the surface approach. BMC Bioinformatics 15, 190 (2014). https://doi.org/10.1186/1471210515190
Received:
Accepted:
Published:
DOI: https://doi.org/10.1186/1471210515190