 Introduction
 Open Access
 Published:
FEPIMB: identifying SNPsdisease association using a Markov Blanketbased approach
BMC Bioinformatics volume 12, Article number: S3 (2011)
Abstract
Background
The interactions among genetic factors related to diseases are called epistasis. With the availability of genotyped data from genomewide association studies, it is now possible to computationally unravel epistasis related to the susceptibility to common complex human diseases such as asthma, diabetes, and hypertension. However, the difficulties of detecting epistatic interaction arose from the large number of genetic factors and the enormous size of possible combinations of genetic factors. Most computational methods to detect epistatic interactions are predictorbased methods and can not find true causal factor elements. Moreover, they are both timeconsuming and sampleconsuming.
Results
We propose a new and fast Markov Blanketbased method, FEPIMB (Fast EPistatic Interactions detection using Markov Blanket), for epistatic interactions detection. The Markov Blanket is a minimal set of variables that can completely shield the target variable from all other variables. Learning of Markov blankets can be used to detect epistatic interactions by a heuristic search for a minimal set of SNPs, which may cause the disease. Experimental results on both simulated data sets and a real data set demonstrate that FEPIMB significantly outperforms other existing methods and is capable of finding SNPs that have a strong association with common diseases.
Conclusions
FEPIMB algorithm outperforms other computational methods for detection of epistatic interactions in terms of both the power and sampleefficiency. Moreover, compared to other Markov Blanket learning methods, FEPIMB is more timeefficient and achieves a better performance.
Background
In recent years, the success of GWAS (genomewide association studies) makes it possible to detect genetic factors that influence the susceptibility to particular diseases in human populations [1]. While most of GWAS search for one single contributing locus at a time, they fail to identify the combinational effect (epistasis) of genetic variants (i.e., singlenucleotide polymorphisms, or SNPs) associated with common complex diseases such as asthma, diabetes, and hypertension [2]. It is well known that epistatic interactions, not individual variant, are critical in unravelling genetic causes of complex human diseases [3]. However, the number of possible combinations of SNPs in a genome is enormous, which is infeasible to be evaluated exhaustively by experimental methods. Therefore, researchers resort to computational methods to detect epistatic interactions based on the genotyped data [2, 4].
Recently, a number of statistical methods have been proposed to detect epistatic interactions. Among these methods, the most commonly used one is logistic regression (LR) [5]. However, logistic regression may not be appropriate for epistasis due to its overfitting problem due to the fact that the number of parameters will be much larger than the available samples. To avoid this shortcoming, Ritchie et al. proposed MDR (multifactor dimensionality reduction) [6, 7], which utilizes the ratio of the number of cases to the number of controls in cells of risk table to reduce the dimensionality to one and select SNP combinations that have the highest prediction performance. The process of labelling each cell of risk table as “high risk” or “low risk” is a process of estimating parameters, which may also result in the overfitting problems when the size of SNP combinations is large. Furthermore, MDR selects the SNP combinations purely by the prediction performance and thus, it may not find true causal factors. Park and Hastie proposed the stepwisepenalized logistic regression (stepPLR) to overcome the drawbacks of logistic regression and MDR [8]. StepPLR makes some simple modifications for standard logistic regression (LR). For example, stepPLR combines the LR criterion with a penalization of the L2norm of the coefficients. This modification makes stepPLR more robust to highorder epistatic interactions. Despite its modifications, stepPLR is timeconsuming when estimating parameters, which is one essential limitation of regression methods. BEAM is a Bayesian marker partition model using Markov Chain Monte Carlo to reach an optimal marker partition and a new B statistic to check each marker or set of markers for significant associations [9]. Note that most statistical methods can not be applied to genomewide analysis directly due to their computational complexity. The alternative approaches to parametric statistical methods are machine learning methods including Support Vector Machine (SVM) [10] and Random Forest [11]. Machine learning methods consider detecting epistatic interactions as a feature selection problem [12] and try to find the best combination of SNPs with the highest prediction accuracy of disease status. Therefore, Chen et al. test three feature selection method: RFE (recursive feature elimination), RFA (recursive feature addition), and GA (genetic algorithm) in [10] and Jiang et al. perform a greedy search in [11]. Like MDR, machine learning methods select SNPs based on classification/prediction accuracy and can not find true causal factors for disease. Moreover, machine learningbased methods tend to introduce many false positives because using more SNPs tends to produce higher classification accuracies.
In this paper, we propose a new and fast Markov Blanket method, FEPIMB (Fast EPistatic Interactions detection using Markov Blanket), to detect epistatic interactions. The Markov Blanket is a minimal set of variables, which can completely shield the target variable from all other variables. As shown in Figure 1, genomewide association studies try to identify the kway interaction among disease SNPs: SNP1, SNP2,…,SNPk and exclude all other unrelated normal SNPs (SNPk+1,…,SNPn). Thus, the Markov Blanket learning method is suitable for detection of epistatic interactions in genomewide casecontrol studies, e.g., to identify a minimal set of SNPs which may cause the disease and require further experiments. Meanwhile the detected minimal set of causal SNPs can shield the disease from all other normal SNPs to decrease the false positive rate and reduce the cost of future validation experiments. Furthermore, Markov Blanket method performs a heuristic search by calculating the association between variables to avoid the timeconsuming training process as in SVM and Random Forest.
Some Markov Blanket methods take a divideandconquer approach that breaks the problem of identifying Markov Blanket of variable T (MB (T)) into two subproblems: first, identifying parents and children of T (PC (T)) and, second, identifying the parents of the children of T (spouse). The goal of epistatic interactions detection is to identify causal interacting genes or SNPs for some certain diseases and therefore it is a special application of Markov Blanket method because we only need to detect the parents of the target variable T (disease status labels). Our new Markov Blanket method makes some simplifications to adapt to this special condition.
We apply the FEPIMB algorithm to simulated datasets based on four disease models and a real dataset (the Agerelated Macular Degeneration (AMD) dataset). We demonstrate that the proposed method significantly outperforms other commonlyused methods and is capable of finding SNPs strongly associated with diseases. Comparing to other Markov Blanket learning methods, our method is faster and can still achieve a better performance.
Results
Simulated data generation
We first evaluate the proposed FEPIMB on simulated data sets, which are generated from three commonly used twolocus epistatic models [5, 9] and one threelocus epistatic model developed [9]. Table 1 lists the disease odds for these four epistatic models, where α is the baseline effect and θ is the genotypic effect. Assume that an individual has genotype g_{ A } at locus A and genotype g_{ B } at locus B in a twolocus epistatic model, then the disease odds are
where p(Dg_{ A },g_{ B }) is the probability that an individual has the disease given genotype (g_{ A },g_{ B }) and is the probability that an individual does not have the disease given genotype (g_{ A },g_{ B }).
In Model1 the odds of disease increase in a multiplicative mode both within and between two loci. For example, an individual with Aa at locus A has larger odds, which are 1 + θ times relative to those of an individual who is homozygous AA; the aa homozygote has further increased disease odds by (1 + θ)^{2}. We can also find similar effects on locus B. Finally the odds of disease for each combination of genotypes at loci A and B can be obtained by the product of the two withinlocus effects. Model2 demonstrates twolocus interaction multiplicative effects because at least one diseaseassociated allele must be present at each locus to increase the odds beyond the baseline level. Moreover the increment of the diseaseassociated allele at loci A or B can further increase the disease odds by the multiplicative factor 1 + θ. Model3 specifies twolocus interaction threshold effects. Like Model 2, Model3 also requires at least one copy of the diseaseassociated alleles at both loci A and B. However the increment of the diseaseassociated allele does not increase the risk further. We call this as disease threshold effect. It means that a single copy of the diseaseassociated allele at each locus is required to increase odds of disease and this is the disease threshold. But after the disease threshold has already been met, having both copies of the diseaseassociated allele at either locus has no additional influence on disease odds. There are three disease loci in model 4. Some certain genotype combinations can increase disease risk and there are almost no marginal effects for each disease locus. Model 4 is more complex than Models 1, 2 and 3. All these four models are nonadditive models and they differ in the way that the number of diseaseassociated allele increases the odds of disease. The prevalence of a disease is the proportion the total number of cases of the disease in the population and we assume that the disease prevalence is 0.1 for all these four disease models [9].
To generate data, we need to determine three parameters associated with each model: the marginal effect of each disease locus (λ), the minor allele frequencies (MAF) of both disease loci, and the strength of linkage disequilibrium (LD) between the unobserved disease locus and a genotyped locus [5]. LD is a nonrandom association of alleles at different loci and is quantified by the squared correlation coefficient r^{2} calculated from allele frequencies [5]. In this paper, we set λ equal to 0.3, 0.3, and 0.6 for models 1, 2, and 3, respectively. For model 4, we set θ = 7 arbitrarily because there are almost no marginal effects in model 4. We let MAF take four values (0.05, 0.1, 0.2, and 0.5) and let r^{2} take two values (0.7, 1.0) for each model. For each nondisease marker we randomly chose its MAF from a uniform distribution in [0.0. 0.5]. We first generate 50 small datasets and each dataset contains 100 markers genotyped for 1,000 cases and 1,000 controls based on each parameter setting for each model. To test the scalability of FEPIMB, we also generate 50 large datasets and each dataset contains 500 markers genotyped for 2,000 cases and 2,000 controls using the same parameter setting for each model.
Epistasis detection on simulated data
We compare the FEPIMB algorithm with three commonlyused methods: BEAM, SVM and MDR on the four simulated disease models. To measure the performance of each method, we use “power” as the criterion function. Power is calculated as the fraction of 50 simulated datasets in which disease associated markers are identified and demonstrate statistically significant associations (G^{2} test values below a threshold for FEPIMB) with the disease [9, 11]. The BEAM software is downloaded from http://www.fas.harvard.edu/~junliu/BEAM and we set the threshold of the B statistic as 0.1 [9]. For SVM, we use LIBSVM with a RBF kernel to detect epistatic interactions and the same searching strategy as shown in [13]. Since MDR algorithm can not be applied to a large dataset directly, we first reduce the number of SNPs to 10 by ReliefF [14], a commonlyused feature selection algorithm, and then MDR performs an exhaustive search for a SNP set that can maximize crossvalidation consistency and prediction accuracy. For the large datasets containing 500 markers genotyped for 2,000 cases and 2,000 controls, we only compare the performance of FEPIMB, BEAM and SVM because ReliefF [14] in MDR can not work for large datasets of this scale.
We show the results on the simulated data in Figures 2 and 3. As can be seen, FEPIMB performs the best comparing to other three methods. BEAM is the second best. In most cases, the powers of MDR are much smaller than these of the FEPIMB and BEAM algorithms. For the MDR algorithm, the poor performance may be due to the use of ReliefF to reduce SNPs from a very large dimensionality. We try another comparison experiment based on the simulated data containing only 40 markers, which makes us be able to apply MDR to the simulated data directly. The performance of MDR is still poor and this indicates that perhaps using the risk table as a predictor to detect epistatic interactions is not a good choice. In some cases, SVM can achieve a comparable or even better performance than FEPIMB and BEAM, however, at the cost of introducing more false positives. Figure 3 also demonstrates the scalability of FEPIMB on large datasets.
An important issue for epistatic interaction detection in genomewide association studies is the number of available samples. Typically, the size of samples is limited and consequently, computational model behaves differently. We explore the effect of the number of samples on the performance of BEAM and FEPIMB (SVM will always introduce a large number of false positives and thus, is not compared here). We generate synthetic datasets containing 40 markers genotyped for different number of cases and controls with r^{2} = 1 and MAF=0.5. The result is shown in Figure 4 and we find that FEPIMB can achieve a higher power than BEAM when the number of samples is the same in most cases. On the other hand, FEPIMB needs fewer samples to reach the perfect power comparing to BEAM. So we can conclude that FEPIMB is more sampleefficient than BEAM.
We also compare the performance of FEPIMB with interIAMBnPC based on the large dataset from model1 to show the time efficiency of FEPIMB. Among the three variants of IAMB, interIAMBnPC can achieve the best performance [15]. Both FEPIMB and interIAMBnPC are written in MATLAB and all the experiments are run on an Intel Core 2 Duo T6600 2.20 GHz, 4GB RAM and Windows Vista. The results are shown in Table 2. As seen, FEPIMB runs more than ten times faster than interIAMBnPC.
Epistasis detection on AMD data
FEPIMB demonstrates its greater power, sampleefficiency, and timeefficiency on simulated data with the number of SNPs less than 500. In practical problems, a typical GWAS genotype dataset contains at least more than 30,000 common SNPs. FEPIMB can also be scalable to largescale datasets in real genomewide casecontrol studies. We apply FEPIMB to an Agerelated Macular Degeneration (AMD) dataset, which contains 116,204 SNPs genotyped with 96 cases and 50 controls [16]. AMD (OMIM 603075) [17] is a common genetic disease related to the progressive visual dysfunction in age over 70 in the developed country. We use the same preprocessing method as in [9, 16]. After filtering, there are 97,327 SNPs lying in 22 autosomal chromosomes remained.
The searching time of FEPIMB for AMDrelated SNPs on an Intel Core 2 Duo T6600 2.20 GHz, 4GB RAM and Windows Vista is 96.4s and FEPIMB detects two associated SNPs: rs380390 and rs2402053, which have a G^{2} test pvalue of 5.36*10^{10}. The first SNP, rs380390, is already found in [16] with a significant association with AMD. The other SNP detected by the FEPIMB algorithm is SNP rs2402053, which is intergenic between TFEC and TES in chromosome 7q31 [18].
It is worth noting that several lines of evidence have previously shown the long arm of 7q harbors genes implicated in retinal disorders. Among which is mapping of a locus on 7q31q32 for retinitis pigmentosa, another retinal disease [19]. Ocular abnormalities have been reported for an individual with terminal deletion of chromosome 7q [20]. Mutations in a gene located at 7q32 have been reported in families with autosomal dominant retinitis pigmentosa [21]. More recently, Nextgeneration sequencing revealed mutations in another gene located on chromosome 7q31 in patients with a form of retinopathy [22].
The rs2402053 SNP identified in our study does not locate in any of the previously reported implicated genes in retinal disorders. Therefore, it may shed light on discovering a new genetic factor, on chromosome 7q, contributing to the underlying mechanism of AMD, a complex form of retinal degenerative disorder. The real mechanism of interaction between rs380390 and rs2402053 should be explored further by biological experiments.
Conclusions
While many computational methods were used for identification of epistatic interactions, most existing computational methods do not consider the complexity of genetic mechanisms causing common diseases and only focus on the selection of SNP sets, which show the best classification capacity. This will introduce many false positives inevitably. Furthermore, most existing methods cannot directly handle genomewide scale problems. In this paper, we introduce a new and fast Markov Blanketbased method, FEPIMB, to identify epistatic interactions. We compared FEPIMB with three other methods, BEAM, SVM and MDR, over both simulated datasets and a real dataset. Our results show that the FEPIMB algorithm outperforms other methods in terms of the power and sampleefficiency. Moreover, we compare FEPIMB with one of the best Markov Blanket learning method, interIAMBnPC. The FEPIMB is more than ten times faster than interIAMBnPC.
Methods
Markov blankets
Bayesian networks represent a joint probability distribution J over a set of random variables by a directed acyclic graph (DAG) G and encode the Markov condition property: each variable is conditionally independent of its nondescendants, given its parents in G[23]. In a Bayesian network, if the probability distribution of X conditioned on both Y and Z is equal to the probability distribution of X conditioned only on Y, i.e., P(XY, Z) = (X  Y), X is conditionally independent of Z given Y. This conditional independence is represented as (X ⊥ ZY).
Definition 1 (Faithfulness). A Bayesian network N and a joint probability distribution J are faithful to each other if and only if every conditional independence entailed by the DAG of N and the Markov Condition is also present in J[24].
Theorem 1. If a Bayesian network N is faithful to a joint probability distribution J, then: (1) nodes X and Y are adjacent in N if and only if X and Y are conditionally dependent given any other set of nodes. (2) for the triplet of nodes X, Y , and Z in N, X and Z are adjacent to Y , but Z is not adjacent to X, X → Y ← Z is a subgraph of N if and only if X and Z are dependent conditioned on every other set of nodes that contains Y .
We can define the Markov Blanket of a variable T, MB (T), as a minimal set for which (X ⊥ TMB(T)), for all X ∈ V – {T} – MB(T) where V is the variable set. The Markov Blanket of a variable T is a minimal set of variables, which can completely shield variable T from all other variables. All other variables are probabilistically independent of the variable T conditioned on the Markov Blanket of variable T.
Theorem 2. If Bayesian network N is faithful to its corresponding joint probability distribution J, then for every variable T, MB(T) is unique and is the set of parents, children, and spouses of T.
Theorem 1 and Theorem 2 are proven in [25, 26], separately. We show an example of the Markov Blanket in the wellknown Asia network in Figure 5. The MB(T) of the node ‘TBorCancer’ is the set of grayfilled nodes.
Given the definition of a Markov Blanket, the probability distribution of T is completely determined by the values of variables in MB(T). Therefore, the detection of Markov Blanket can be applied for optimal variable selection and causal discovery. In this paper, we use Markov Blanket method to detect potential causal SNPs for common complex diseases.
Markov blankets learning methods
There are several Markov Blanket learning methods such as: KollerSahami (KS) algorithm [27], GrowShrink (GS) algorithm [28], Incremental association Markov Blanket (IAMB) algorithm [15], MaxMin Markov Blanket (MMMB) algorithm [29], HITON_MB [30] and PCMB [31].
KollerSahami (KS) algorithm is the first algorithm to employ Markov Blanket for feature selection. However, there is no theoretical guarantee for KollerSahami (KS) algorithm to find optimal MB set [27]. The GS algorithm [24] and IAMB methods [15] are two similar algorithms with two search procedures, forward and backward. In the forward phase, the nodes of MB(T) are admitted into MB, while in the backward phase false positives are removed from MB. Under the assumptions of faithfulness and correct independence test, both the GS algorithm and IAMB are proved correct [15]. Comparing to GS algorithm, IAMB might achieve a better performance with fewer false positives admitted during the forward phase. A common limitation for GS algorithm and IAMB is that both methods require a very large number of samples to perform well. IAMB can be revised in two ways: (1) After each admission step in forward phase, perform a backward conditioning phase to remove false positives to keep the size of MB(T) as small as possible. (2) Substitute the backward conditioning phase with the PC algorithm instead [20]. In other words, the backward phase will perform the independence test conditioned on all subsets of the current Markov Blanket. Tsamardinos et al. proposed three IAMB variants: interIAMB, IAMBnPC and InterIAMBnPC [15]. They also proved the correctness of InterIAMBnPC. The time complexity of IAMB is O(MB×N) where MB is the size of MB and N is number of variables.
To overcome the data inefficient problem of IAMB and its variants, MaxMin Markov Blanket (MMMB) algorithm [29], HITON_MB [30] and PCMB [31] are proposed. All these three algorithms take a divideandconquer method that breaks down the problem of identifying Markov Blanket of variable T into two subproblems: First, identifying parents and children of T (PC(T)) and, second, identifying the spouses of T. Meanwhile, they have the same two assumptions as IAMB (i.e. faithfulness and correct independence test) and take into account the graph topology to improve data efficiency. However, results from MMPC/MB and HITONPC/MB are not always correct since some descendants of T other than its children will enter PC(T) during the first step of identifying parents and children of T [31]. PCMB can be proved correct in [31]. In every loop, PCMB first remove unrelated variables, then PCMB use IAMBnPC method to admit one feature and remove false positives. The problem of PCMB is that the PC algorithm performs an exhaustive conditional independence test, which is very time consuming. The reason that PC algorithm was used in PCMB and interIAMBnPC is that PC algorithm is a more sampleefficient method and is sound under the assumption of faithfulness [15]. In fact if the size of Markov Blanket is large, PC algorithm still needs a lot of samples to guarantee its performance. There is no theoretical proof and guarantee that the PC algorithm admits less false positives than other methods.
Method description: FEPIMB
Detecting genegene interaction is a special application of Markov Blanket learning method because we only need to detect the parents of the target variable T and don’t need to design a complex algorithm to detect spouses of T. Here target variable T is the disease status labels and the parents of T are those disease SNPs. MB(T) only contains the parents of T.
All Markov Blanket learning methods are based on the following two Theorems.
Theorem 3. If a variable belongs to MB(T) which only contains the parents of T, then it will be dependent on T given any subset of the variable set V{T} .
Proof: This is a direct consequence of Theorem 1 because now MB(T) only contains the parents of T. □
Theorem 4. If a variable is not a member of MB(T), then conditioned on MB(T), or any superset of MB(T), it will be independent of T.
Proof: Let X, Y, Z and W represent four mutually disjoint variable sets. Any probability distribution p satisfies the weak union property: [25]. Based on the definition of Markov Blanket, we get that . Thus, by the weak union property, we have for any subset .□
The G^{2} test is used to test independence and conditional independence between two variables for discrete data [13, 24, 32]. The null hypothesis for G^{2} test is that two variables are independent. As described next, the proposed FEPIMB uses G^{2} to test the association and independence between SNPs and disease status.
The detail of our FEPIMB algorithm is shown in Figure 6. It consists of three phases: RemoveMB, Forward MB and Backward MB. During the phase of RemoveMB, unrelated variables are removed from the candidate set for Markov Blanket (canMB) based on the conditional independence test. This will reduce the searching space after each iteration and can help to decrease the computational complexity. After the phase of RemoveMB, the variable which has the maximal G^{2} score and is associated with the target variable T in canMB enters MB(T) in the phase of Forward MB, where false positives are removed during the phase of Backward MB. Comparing to PCMB, we get rid of the timeconsuming PC algorithm and use the maximal subset of current MB(T) to perform the conditional independence test in the phase of Backward MB. The time complexity of FEPIMB is less than the O(MB×N) of IAMB because in each iteration after the first iteration the number of conditional independence tests performed in the phase of RemoveMB is less than N. The optimal time complexity of FEPIMB is O(N).
Like IAMB and PCMB, the soundness of FEPIMB is based on the assumptions of DAGfaithfulness and correct independence test.
Theorem 5. Under the assumptions that the independence tests are correct and that the data D are generated from a probability distribution which is faithful to a DAG G, FEPIMB returns all parents of T.
Proof: First, each node in MB(T) enters MB(T) in the Forward MB phase and will not be removed during the Backward MB phase because if , then for any owing to Theorem 3. Second, the nodes outside the MB(T) will be removed sooner or later during the Backward MB phase especially after all elements in the Markov Blanket of T enter the current MB(T) because of the definition of Markov Blanket and Theorem 4. □
Even though FEPIMB is a method based on the greedy algorithm, Theorem 3 and Theorem 4 can guarantee that FEPIMB will not get stuck in a local optimum.
Abbreviations
 GWAS:

genomewide association studies
 FEPIMB:

Fast EPistatic Interactions detection using Markov Blanket
 SNP:

single nucleotide polymorphisms
 LR:

logistic regression
 MDR:

multifactor dimensionality reduction
 stepPLR:

stepwise penalized logistic regression
 BEAM:

Bayesian epistasis association mapping
 MCMC:

Markov Chain Monte Carlo
 SVM:

Support Vector Machine
 RFE:

recursive feature elimination
 RFA:

recursive feature addition
 GA:

genetic algorithm
 AMD:

Agerelated Macular Degeneration
 MAF:

minor allele frequencies
 LD:

linkage disequilibrium
 HWE:

HardyWeinberg Equilibrium
 DAG:

directed acyclic graph.
References
 1.
Hirschhorn JN, Daly MJ: Genomewide association studies for common diseases and complex traits. Nat Rev Genet 2005, 6: 95–108.
 2.
McKinney BA, Reif DM, Ritchie MD, Moore JH: Machine learning for detecting genegene interactions: a review. Appl Bioinformatics 2006, 5: 77–88. 10.2165/0082294220060502000002
 3.
Cordell HJ: Epistasis: what it means, what it doesn't mean, and statistical methods to detect it in humans. Hum Mol Genet 2002, 11: 2463–2468. 10.1093/hmg/11.20.2463
 4.
Musani SK, Shriner D, Liu N, Feng R, Coffey CS, Yi N, Tiwari HK, Allison DB: Detection of gene x gene interactions in genomewide association studies of human population data. Hum Hered 2007, 63: 67–84. 10.1159/000099179
 5.
Marchini J, Donnelly P, Cardon LR: Genomewide strategies for detecting multiple loci that influence complex diseases. Nature genetics 2005, 37: 413–417. 10.1038/ng1537
 6.
Ritchie MD, Hahn LW, Moore JH: Power of multifactor dimensionality reduction for detecting genegene interactions in the presence of genotyping error, missing data, phenocopy, and genetic heterogeneity. Genetic epidemiology 2003, 24: 150–157. 10.1002/gepi.10218
 7.
Ritchie MD, Hahn LW, Roodi N, Bailey LR, Dupont WD, Parl FF, Moore JH: Multifactordimensionality reduction reveals highorder interactions among estrogenmetabolism genes in sporadic breast cancer. American journal of human genetics 2001, 69: 138–147. 10.1086/321276
 8.
Park MY, Hastie T: Penalized logistic regression for detecting gene interactions. Biostatistics (Oxford, England) 2008, 9: 30–50.
 9.
Zhang Y, Liu JS: Bayesian inference of epistatic interactions in casecontrol studies. Nature genetics 2007, 39: 1167–1173. 10.1038/ng2110
 10.
Chen SH, Sun J, Dimitrov L, Turner AR, Adams TS, Meyers DA, Chang BL, Zheng SL, Gronberg H, Xu J, Hsu FC: A support vector machine approach for detecting genegene interaction. Genetic epidemiology 2008, 32: 152–167. 10.1002/gepi.20272
 11.
Jiang R, Tang W, Wu X, Fu W: A random forest approach to the detection of epistatic interactions in casecontrol studies. BMC bioinformatics 2009, 10(Suppl 1):S65. 10.1186/1471210510S1S65
 12.
Guyon I, Elisseeff A: An introduction to variable and feature selection. J Mach Learn Res 2003, 3: 1157–1182.
 13.
Han B, Park M, Chen XW: A Markov blanketbased method for detecting causal SNPs in GWAS. BMC bioinformatics 2010, 11(Suppl 3):S5. 10.1186/1471210511S3S5
 14.
RobnikŠikonja M, Kononenko I: Theoretical and empirical analysis of ReliefF and RReliefF. Machine learning 2003, 53: 23–69. 10.1023/A:1025667309714
 15.
Tsamardinos I, Aliferis C, Statnikov A, Statnikov E: Algorithms for Large Scale Markov Blanket Discovery. In Proceedings of the 16th International FLAIRS Conference: 11–15 May 2003; St. Augustine. Edited by: Doug Dankel. Menlo Park: AAAI Press; 2003:376–380.
 16.
Klein RJ, Zeiss C, Chew EY, Tsai JY, Sackler RS, Haynes C, Henning AK, SanGiovanni JP, Mane SM, Mayne ST, et al.: Complement factor H polymorphism in agerelated macular degeneration. Science (New York, NY) 2005, 308: 385–389. 10.1126/science.1109557
 17.
Hamosh A, Scott AF, Amberger J, Bocchini C, Valle D, McKusick VA: Online Mendelian Inheritance in Man (OMIM), a knowledgebase of human genes and genetic disorders. Nucleic Acids Res 2002, 30: 52–55. 10.1093/nar/30.1.52
 18.
Tobias ES, Hurlstone AF, MacKenzie E, McFarlane R, Black DM: The TES gene at 7q31.1 is methylated in tumours and encodes a novel growthsuppressing LIM domain protein. Oncogene 2001, 20: 2844–2853. 10.1038/sj.onc.1204433
 19.
McGuire RE, Gannon AM, Sullivan LS, Rodriguez JA, Daiger SP: Evidence for a major gene (RP10) for autosomal dominant retinitis pigmentosa on chromosome 7q: linkage mapping in a second, unrelated family. Hum Genet 1995, 95(1):71–4.
 20.
Reynolds JD, Golden WL, Zhang Y, Hiles DA: Ocular abnormalities in terminal deletion of the long arm of chromosome seven. J Pediatr Ophthalmol Strabismus 1984, 21(1):28–32.
 21.
Bowne SJ, Sullivan LS, Blanton SH, Cepko CL, Blackshaw S, Birch DG: HughbanksWheaton D, Heckenlively JR, Daiger SP: Mutations in the inosine monophosphate dehydrogenase 1 gene (IMPDH1) cause the RP10 form of autosomal dominant retinitis pigmentosa. Hum Mol Genet 2002, 11(5):559–68. 10.1093/hmg/11.5.559
 22.
Nikopoulos K, Gilissen C, Hoischen A, van Nouhuys CE, Boonstra FN, Blokland EA, Arts P, Wieskamp N, Strom TM, Ayuso C, Tilanus MA, Bouwhuis S, Mukhopadhyay A, Scheffer H, Hoefsloot LH, Veltman JA, Cremers FP, Collin RW: Nextgeneration sequencing of a 40 Mb linkage interval reveals TSPAN12 mutations in patients with familial exudative vitreoretinopathy. Am J Hum Genet 2010, 86(2):240–7. 10.1016/j.ajhg.2009.12.016
 23.
Chen XW, Anantha G, Lin X: Improving Bayesian Network Structre Learning with Mutual InformationBased Node Ordering in the K2 Algorithm. IEEE Trans on Knowl and Data Eng 2008, 20: 628–640.
 24.
Spirtes P, Glymour CN, Scheines R: Causation, prediction, and search. 2nd edition. Cambridge, Mass.: MIT Press; 2000.
 25.
Pearl J: Probabilistic reasoning in intelligent systems : networks of plausible inference. San Mateo, Calif.: Morgan Kaufmann Publishers; 1988.
 26.
Tsamardinos I, Aliferis C: Towards Principled Feature Selection: Relevancy, Filters and Wrappers. In Proceedings of the Ninth International Workshop on Artificial Intelligence and Statistics: Jan 3–6, 2003; Key West, Florida. Edited by: Edited by Christopher M. Bishop and Brendan J. Frey. San Fransisco: Morgan Kaufmann; 2003.
 27.
Koller D, Sahami M: Toward Optimal Feature Selection. In Proceedings of 13th conference on machine learning: 3–6 Jyly 1996; Bari, Italy. Volume 3. Edited by: Lorenza Saitta. San Fransisco: Morgan Kaufmann; 1996:284–292.
 28.
Margaritis D, Thrun S: Bayesian Network Induction via Local Neighborhoods. In Proceedings of Neural Information Processing Systems 12:29 Nov4 Dec 1999; Denver. Edited by: Sara A. Solla, Todd K. Leen and KlausRobert Müller. Cambridge: MIT Press; 1999:505–511.
 29.
Tsamardinos I, Aliferis C, Statnikov A: Time and Sample Efficient Discovery of Markov Blankets And Direct Causal Relations. In Proceedings of the ninth ACM SIGKDD international conference on Knowledge discovery and data mining: 24–27 August 2003; Washington, D.C. Volume 24. Edited by: Lise Getoor. New York: ACM; 2003:673–678.
 30.
Aliferis CF, Tsamardinos I, Statnikov A: HITON: a novel Markov Blanket algorithm for optimal variable selection. AMIA Annu Symp Proc 2003, 21–25.
 31.
Peña JM, Nilsson R, Björkegren J, Tegnér J: Towards scalable and data efficient learning of Markov boundaries. International Journal of Approximate Reasoning 2006, 45: 211–232.
 32.
Sokal RR, Rohlf FJ: Biometry : the principles and practice of statistics in biological research. 3rd edition. New York: Freeman; 1995.
Acknowledgements
This work is supported by the US National Science Foundation Award IIS0644366.
Author information
Affiliations
Corresponding author
Additional information
Competing interests
The authors declare that they have no competing interests.
Authors' contributions
BH designed and implemented the FEPIMB method, tested the existing methods and analyzed experimental results. XWC conceived the study, designed the experiments, and analyzed experimental results. ZT analyzed experimental results. All authors helped in drafting the manuscript and approved the final manuscript.
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
Han, B., Chen, Xw. & Talebizadeh, Z. FEPIMB: identifying SNPsdisease association using a Markov Blanketbased approach. BMC Bioinformatics 12, S3 (2011). https://doi.org/10.1186/1471210512S12S3
Published:
DOI: https://doi.org/10.1186/1471210512S12S3