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BMC Bioinformatics

, 20:40 | Cite as

Comparative analysis of differential gene expression analysis tools for single-cell RNA sequencing data

  • Tianyu Wang
  • Boyang Li
  • Craig E. Nelson
  • Sheida NabaviEmail author
Open Access
Research article
Part of the following topical collections:
  1. Sequence analysis (methods)

Abstract

Background

The analysis of single-cell RNA sequencing (scRNAseq) data plays an important role in understanding the intrinsic and extrinsic cellular processes in biological and biomedical research. One significant effort in this area is the detection of differentially expressed (DE) genes. scRNAseq data, however, are highly heterogeneous and have a large number of zero counts, which introduces challenges in detecting DE genes. Addressing these challenges requires employing new approaches beyond the conventional ones, which are based on a nonzero difference in average expression. Several methods have been developed for differential gene expression analysis of scRNAseq data. To provide guidance on choosing an appropriate tool or developing a new one, it is necessary to evaluate and compare the performance of differential gene expression analysis methods for scRNAseq data.

Results

In this study, we conducted a comprehensive evaluation of the performance of eleven differential gene expression analysis software tools, which are designed for scRNAseq data or can be applied to them. We used simulated and real data to evaluate the accuracy and precision of detection. Using simulated data, we investigated the effect of sample size on the detection accuracy of the tools. Using real data, we examined the agreement among the tools in identifying DE genes, the run time of the tools, and the biological relevance of the detected DE genes.

Conclusions

In general, agreement among the tools in calling DE genes is not high. There is a trade-off between true-positive rates and the precision of calling DE genes. Methods with higher true positive rates tend to show low precision due to their introducing false positives, whereas methods with high precision show low true positive rates due to identifying few DE genes. We observed that current methods designed for scRNAseq data do not tend to show better performance compared to methods designed for bulk RNAseq data. Data multimodality and abundance of zero read counts are the main characteristics of scRNAseq data, which play important roles in the performance of differential gene expression analysis methods and need to be considered in terms of the development of new methods.

Keywords

Single-cell RNAseq Differential gene expression analysis Comparative analysis 

Abbreviations

AUC

Area under curve

DB

Both DM and DU

DM

Differential modality

DP

Differential proportion

DPM

Dirichlet process mixture

DU

Differential unimodal

FDRs

False discovery rates

FN

False negative

FP

False positive

FPR

False positive rate

GAMs

Generalized additive models

NB

Negative binomial

NGS

Next generation sequencing

RNAseq

RNA sequencing

ROC

Receiver operating characteristic

scRNAseq

Single Cell RNA sequencing

TMM

Trimmed mean of M-values

TN

True negative

TNR

True negative rate

TP

True positive

TPM

Transcript per million

TPR

True positive rate

ZINB

Zero-inflated negative binomial

Background

Next generation sequencing (NGS) [1] technologies greatly promote research in genome-wide mRNA expression data. Compared with microarray technologies, NGS provides higher resolution data and more precise measurement of levels of transcripts for studying gene expression. Through downstream analysis of RNA sequencing (RNAseq) data, gene expression levels reveal the variability between different samples. Typically, in RNAseq data analysis, the expression value of a gene from one sample represents the mean of all expression values of the bulk population of cells. Although it is common to use expression values on such a bulk scale in certain situations [2, 3, 4], it is not sufficient to employ bulk RNAseq data for other biological research that involves, for example, studying circulating tumor cells [5] and stem cells. Consequently, analyzing gene expression values on the single-cell scale provides deep insight into the interplay between intrinsic cellular processes and stochastic gene expression in biological and biomedical research [6, 7, 8, 9]. For example, single-cell data analysis is important in cancer studies, as differential gene expression analysis between different cells can help to uncover driver genes [10].

Tools developed for differential gene expression analysis on bulk RNAseq data, such as DESeq [11] and edgeR [12], can be applied to single-cell data [11, 12, 13, 14, 15, 16, 17, 18, 19, 20]. Single-cell RNAseq (scRNAseq) data, however, have different characteristics from those of bulk RNAseq data that require the use of a new differential expression analysis definition, beyond the conventional definition of a nonzero difference in average expression. In scRNAseq data, due to the tiny number and low capture efficiency of RNA molecules in single cells [6], many transcripts tend to be missed during the reverse transcription. As a result, we may observe that some transcripts are highly expressed in one cell but are missed in another cell. This phenomenon is defined as a “drop-out” event [21]. Recent studies have shown that gene expression in a single cell is a stochastic process and that gene expression values in different cells are heterogeneous [22, 23], which results in multimodality in expression values in different cells. For example, cells from the same brain tissue or the same tumor [24] pose huge heterogeneity from cell to cell [24, 25, 26, 27, 28]. Even though they are from the same tissue, these cells are different in regard to cell types, biological functions, and response to drugs. Therefore, unlike bulk RNAseq data, scRNAseq data tend to exhibit an abundance of zero counts, a complicated distribution, and huge heterogeneity. Examples of distributions of scRNAseq expression values between two conditions are shown in Fig. 1. Consequently, the heterogeneity within and between cell populations manifests major challenges to the differential gene expression analysis in scRNAseq data.
Fig. 1

Distributions of gene expression values of total 92 cells in two groups (ES and MEF) using real data show that scRNAseq data exhibit a different types of multimodality (DU, DP, DM, and DB) and b large amounts of zero counts. X axis represents log-transformed expression values. To clearly show the multimodality of scRNAseq data, zero counts are removed from the distribution plots in (a)

To address the challenges of multimodal expression values and/or drop-out events, new strategies and models [21, 29, 30, 31, 32, 33, 34, 35, 36, 37] have been proposed for scRNAseq data. Single-cell differential expression (SCDE) [21] and model-based analysis of single-cell transcriptomics (MAST) [29] use a two-part joint model to address zero counts; one part corresponds to the normal observed genes, and the other corresponds to the drop-out events. Monocle2 [38] is updated from the previous Monocle [32] and employs census counts rather than normalized transcript counts as input to better normalize the counts and eliminate variability in single-cell experiments. A recent approach, termed scDD [39], considers four different modality situations for gene expression value distributions within and across biological conditions. DEsingle employs a zero-inflated negative binomial (ZINB) regression model to estimate the proportion of the real and drop-out zeros and classifies the differentially expressed (DE) genes into three categories. Recently, nonparametric methods, SigEMD [37], EMDomics [31], and D3E [33], have been proposed for differential gene expression analysis of heterogeneous data. Without modeling the distributions of gene expression values and estimating their parameters, these methods identify DE genes by employing a distance metric between the distributions of genes in two conditions.

A few studies have compared differential expression analysis methods for scRNAseq data. Jaakkola et al. [40] compared five statistical analysis methods for scRNAseq data, three of which are for bulk RNAseq data analysis. Miao et al. [41] evaluated 14 differential expression analysis tools, three of which are newly developed for scRNAseq data and 11 of which are old methods for bulk RNAseq data. A recent comparison study [42] assessed six differential expression analysis tools, four of which were developed for scRNAseq and two of which were designed for bulk RNAseq. In this study, we consider all differential gene expression analysis tools that have been developed for scRNAseq data as of October 2018 (SCDE [21], MAST [29], scDD [39], D3E [33], Monocle2 [38], SINCERA [34], DEsingle [36], and SigEMD [37]). We also consider differential gene expression analysis tools that are designed for heterogeneous expression data (EMDomics [31]) and are commonly used for bulk RNAseq data (edgeR [4], DESeq2 [43]).

The goal of this study is to reveal the limitations of the current tools and to provide insight and guidance in regard to choosing a tool or developing a new one. In this work, we discuss the computational methods used by these tools and comprehensively evaluate and compare the performance of the tools in terms of sensitivity, false discover rate, and precision. We use both simulated and real data to evaluate the performance of the above-noted tools. To generate more realistic simulated data, we model both multimodality and drop-out events in simulated data. Using gold standard DE genes in both simulated and real data, we evaluate the accuracy of detecting true DE genes. In addition, we investigate the agreement among the methods in identifying significantly DE genes. We also evaluate the effect of sample size on the performance of the tools, using simulated data, and compare the runtimes of the tools, using real data. Finally, we perform gene-set enrichment and pathway analysis to evaluate the biological functional relevance of the DE genes identified by each tool.

Methods

As of October 2018, we have identified eight software tools for differential expression analysis of scRNAseq data, which are designed specifically for such data [21, 29, 30, 33, 34, 36, 37, 38] (SCDE, MAST, scDD, D3E, Monocle2, SINCERA, DEsingle, and SigEMD). We also considered tools designed for bulk RNAseq data that are widely used [4, 43] (edgeR, and DESeq2) or can apply to multimodal data [31] (EMDomics). The general characteristics of the eleven tools are provided in Table 1. MAST, scDD, EMDomics, Monocle2, SINCERA, and SigEMD use normalized TPM/FPKM expression values as input, while SCDE, D3E, and DEsingle use read counts obtained from RSEM as input. D3E runs on Python, while all other methods are developed as an R package. In the following sections, we provide the details of the tools.
Table 1

Software tools for identifying DE genes using scRNAseq data

Tool

Prog. Language

Input format

Model

Year/ version

URL

SCDE

R

Read counts

Poisson and negative binomial model

2014/2.2.0

http://bioconductor.org/packages/release/bioc/html/scde.html

MAST

R

TPM/FPKM

Generalized linear model

2015/1.0.5

http://bioconductor.org/packages/release/bioc/html/MAST.html

scDD

R

TPM/FPKM

Conjugate Dirichlet process mixture

2016/0.99.0

http://bioconductor.org/packages/devel/bioc/html/scDD.html

EMDomics

R

TPM/FPKM

Non-parametric earth mover’s distance

2016/2.4.0

https://www.bioconductor.org/packages/release/bioc/html/EMDomics.html

D3E

Python

Read counts

Cramér-von Mises test, Kolmogorov-Smirnov test, likelihood ratio test

2016/

https://github.com/hemberg-lab/D3E

Monocle2

R

TPM/FPKM

Generalized additive model

2014/2.2.0

http://bioconductor.org/packages/release/bioc/html/monocle.html

SINCERA

R

TPM/FPKM/Read counts

Welch’s t-test and Wilcoxon rank sum test

2015/

https://research.cchmc.org/pbge/sincera.html

edgeR

R

Read counts

Negative binomial model, Exact test

2010/3.16.5

http://bioconductor.org/packages/release/bioc/html/edgeR.html

DESeq2

R

Read counts

Negative binomial model, Exact test

2014/1.14.1

http://bioconductor.org/packages/release/bioc/html/DESeq2.html

DEsingle

R

Read counts

Zero inflated negative binomial

2018/1.2.0

https://bioconductor.org/packages/release/bioc/html/DEsingle.html

SigEMD

R

TPM/FPKM

Non-parametric earth mover’s distance

2018/0.21.1

https://github.com/NabaviLab/SigEMD

Differential gene expression analysis methods for scRNAseq data

Single-cell differential expression (SCDE)

SCDE [21] utilizes a mixture probabilistic model for gene expression values. The observed read counts of genes are modeled as a mixture of drop-out events by a Poisson distribution and amplification components by a negative binomial (NB) distribution:
$$ \left\{\begin{array}{c}{r}_c\sim NB(e)\ \mathrm{for}\ \mathrm{normal}\ \mathrm{amplified}\ \mathrm{genes}\\ {}{r}_c\sim Possion\left({\lambda}_0\right)\ \mathrm{for}\ \mathrm{drop}-\mathrm{out}\ \mathrm{genes}\end{array}\ \right., $$
where e is the expected expression value in cells when the gene is amplified, and λ0 is always set to 0.1. The posterior probability of a gene expressed at level x in cell c based on observed rc and the fitted model Ωc is calculated by:
$$ p\left(x|{r}_c,{\Omega}_c\right)={p}_d(x){p}_{Possion}\left(x|{r}_c\right)+\left(1-{p}_d(x)\right){p}_{NB}\left(x|{r}_c\right), $$
where pd is the probability of a drop-out event in cell c for a gene expressed at an average level x, and ppoisson(x| rc) and pNB(x|rc) are the probabilities of observing expression value rc in the cases of drop-out (Poisson) and successful amplification (NB) of a gene expressed at level x in cell c, respectively. Then, after the bootstrap step, the posterior probability of a gene expressed at level x in a subpopulation of cells S is determined as an expected value:
$$ {p}_s(x)=E\left[{\prod}_{c\in B}p\left(x|{r}_c,{\Omega}_c\right)\right], $$
where B is the bootstrap samples of S. Based on the posterior probabilities of gene expression values in cells S and G, pS(x) and pG(x), SCDE uses a fold expression difference f in gene g for the differential expression analysis between subgroups S and G, which is determined as:
$$ p(f)={\sum}_{x\in X}{p}_S(x){p}_G(x), $$
where X is the expression range of the gene g. An empirical p-value is determined to test the differential expression.

Model-based analysis of single-cell transcriptomics (MAST)

MAST [29] proposes a two-part generalized linear model for differential expression analysis of scRNAseq data. One part models the rate of expression level, using logistic regression:
$$ logit\left(p\left({Z}_{ig}=1\right)\right)={X}_i{\beta}_g^D, $$
where Z = [Zig] indicates whether gene g is expressed in cell i.
The other part models the positive expression mean, using a Gaussian linear model:
$$ p\left({Y}_{ig}=y|{Z}_{ig}=1\right)=N\left({X}_i{\beta}_g^C,{\sigma}_g^2\right), $$
where Y = [yig] is the expression level of gene g in cell i observed Zig = 1. The cellular detection rate (CDR) for each cell, defined as CDRi = (1/N)∑g = 1Zig (N is the total number of genes), is introduced as a column in the design matrix Xi of the logistic regression model and the Gaussian linear model. For the differential expression analysis, a test with asymptotic chi-square null distribution is utilized, and a false discovery rate (FDR) adjustment control [44] is used to decide whether a gene is differentially expressed.

Bayesian modeling framework (scDD)

scDD [39] employs a Bayesian modeling framework to identify genes with differential distributions and to classify them into four situations: 1—differential unimodal (DU), 2—differential modality (DM), 3—differential proportion (DP), and 4—both DM and DU (DB), as shown in Additional file 1: Figure S1. The DU situation is one in which each distribution is unimodal but the distributions across the two conditions have different means. The DP situation involves genes with expression values that are bimodally distributed. The bimodal distribution of gene expression values in each condition has two modes with different proportions, but the two modes across the two conditions are the same. DM and DB situations both include genes whose expression values follow a unimodal distribution in one condition but a bimodal distribution in the other condition. The difference is that, in the DM situation, one of the modes of the bimodal distribution is equal to the mode of the unimodal distribution, whereas in the DB situation, there is no common mode across the two distributions.

Let Yg be the expression value of gene g in a collection of cells. The non-zero expression values of gene g are modeled as a conjugate Dirichlet process mixture (DPM) model of normals, and the zero expression values of gene g are modeled using logistic regression as a separate distributional component:
$$ \left\{\begin{array}{c}\mathrm{nonzero}\ {Y}_g\sim \mathrm{conjugate}\ \mathrm{DPM}\ \mathrm{of}\ \mathrm{normals}\\ {}\mathrm{zero}\ {Y}_g\sim \mathrm{logistic}\ \mathrm{regression}\end{array}\right. $$
For detecting the DE genes, a Bayes factor for gene g is determined as:
$$ {BF}_g=\frac{f\left({Y}_g|{M}_{DD}\right)}{f\left({Y}_g|{M}_{ED}\right)}, $$
where f(Yg| MDD) is the predictive distribution of the observed expression value from gene g under a given hypothesis, MDD denotes the differential distribution hypothesis, and MED denotes the equivalent distribution hypothesis that ignores conditions. As there is no solution for the Bayes factor BFg, a closed form is calculated to present the evidence of whether a gene is differentially expressed:
$$ Scor{e}_g=\log \frac{f\left({Y}_g,{Z}_g|{M}_{DD}\right)}{f\left({Y}_g,{Z}_g|{M}_{ED}\right)}=\log \frac{f_{C1}\left({Y}_g^{C1},{Z}_g^{C1}\right){f}_{C2}Y\left({}_g^{C2},{Z}_g^{C2}\right)}{f_{C1,C2}\left({Y}_g,{Z}_g\right)}, $$
where Zg is the vector of the mean and the variance for gene g, and C1 and C2 represent the two conditions.

EMDomics

EMDomics [31], a nonparametric method based on Earth Mover’s Distance (EMD), is proposed to reflect the overall difference between two normalized distributions by computing the EMD score for each gene and determining the estimation of FDRs. Suppose P = {(p1,wp1),(p2,wp2)…(pm,wpm)} and Q = {(q1,wq1),(q2,wq2)… (qn,wqn)} are two signatures, where pi and qj are the centers of each histogram bin, and wpi and wqj are the weights of each histogram bin. The COST is defined as the summation of the multiplication of flow fij and the distance dij:
$$ COST\left(P,Q,F\right)={\sum}_{i=1}^m{\sum}_{j=1}^n{f}_{ij}{d}_{ij}, $$
where dij is the Euclidean distance between pi and qj, and fij is the amount of weight that need to be moved between pi and qj. An optimization algorithm is used to find a flow F = [fij] between pi and qj to minimize the COST. After that, the EMD score is calculated as the normalized minimum COST.
$$ EMD\left(P,Q\right)=\frac{\sum_{i=1}^m{\sum}_{j=1}^n{f}_{ij}{d}_{ij}}{\sum_{i=1}^m{\sum}_{j=1}^n{f}_{ij}} $$

A q-value, based on the permutations of FDRs, is introduced to describe the significance of the score for each gene.

Monocle2

Monocle2 [38] is an updated version of Monocle [32], a computational method used for cell type identification, differential expression analysis, and cell ordering. Monocle applies a generalized additive model, which is a generalized linear method with linear predictors that depend on some smoothing functions. The model relates a univariate response variable Y, which belongs to the exponential family, to some predictor variables, as follows:
$$ h\left(E(Y)\right)={\beta}_0+{f}_1\left({x}_1\right)+{f}_2\left({x}_2\right)+\dots +{f}_m\left({x}_m\right), $$
where h is the link function, such as identity or log function, Y is the gene expression level, xi is the predictor variable that expresses the cell categorical label, and fi is a nonparametric function, such as cubic splines or some other smoothing functions. Specifically, the gene expression level Y is modeled using a Tobit model:
$$ Y=\left\{\begin{array}{c}{Y}^{\ast }\ if\ {Y}^{\ast }>\lambda \\ {}\lambda\ if\ {Y}^{\ast}\le \lambda \end{array}\right., $$
where Y* is a latent variable that corresponds to predictor x, and λ is the detection threshold. For identifying DE genes, we use an approximate chi-square (χ2) likelihood ratio test.

In Monocle2, a census algorithm is used to estimate the relative transcript counts, which leads to an improvement of the accuracy compared with using the normalized read counts, such as TPM values.

Discrete distributional differential expression (D3E)

D3E [33] consists of four steps: 1—data filtering and normalization, 2—comparing distributions of gene expression values for DE genes analysis, 3—fitting a Poisson-Beta model, and 4—calculating the changes in parameters between paired samples for each gene. For the normalization, D3E uses the same algorithm as used by DESeq2 [11] and filters genes that are not expressed in any cell. Then, the non-parametric Cramer-von Mises test or the Kolmogorov-Smirnov test is used to compare the expression values’ distributions of each gene for identifying the DE genes. Alternatively, a parametric method, the likelihood ratio test, can be utilized after fitting a Poisson-Beta model:
$$ {\displaystyle \begin{array}{c} PB\left(n|\alpha, \beta, \gamma, \lambda \right)= Poisson\left(n|\frac{\gamma x}{\lambda}\right)\underset{x}{\bigwedge \limits } Beta\left(x|\alpha, \beta \right)\\ {}=\frac{\gamma^n{e}^{-\frac{\gamma }{\lambda }}\varGamma \left(\frac{\alpha }{\lambda }+\frac{\beta }{\lambda}\right)}{\lambda^n\varGamma \left(n+1\right)\varGamma \left(\frac{\alpha }{\lambda }+\frac{\beta }{\lambda }+n\right)\varGamma \left(\frac{\alpha }{\lambda}\right)}\varPhi \left(\frac{\alpha }{\lambda },\frac{\alpha }{\lambda }+\frac{\beta }{\lambda }+n,\frac{\gamma }{\lambda}\right)\end{array}}, $$
where n is the number of transcripts of a particular gene, α is the rate of promoter activation, β is the rate of promoter inactivation, γ is the rate of transcription when the promoter is in the active state, λ is the transcript degradation rate, and x is the auxiliary variable. The parameters α, β, and γ can be estimated by moments matching or Bayesian inference method, but λ should be known and assumed to be constant.

SINCERA

SINCERA [34] is a computational pipeline for single cell downstream analysis that enables pre-processing, normalization, cell type identification, differential expression analysis, gene signature prediction, and key transcription factors identification. SINCERA calculates the p-value for each gene from two groups based on a statistical test to identify the DE genes. It provides two methods: one-tailed Welch’s t-test for genes, assuming they are from two independent normal distributions, and the Wilcoxon rank sum test for small sample sizes. Last, the FDRs are adjusted, using the Benjamini and Hochberg method [44].

edgeR

edgeR [4] is a negative binomial model-based method to determine DE genes. It uses a weighted trimmed mean of the log expression ratios to normalize the sequencing depth and gene length between the samples. Then, the expression data are used to fit a negative binomial model, whereby the mean μ and variance ν have a relationship of ν  = μ + αμ2, and α is the dispersion factor. To estimate the dispersion factor, edgeR combines a common dispersion across all the genes, estimated by a likelihood function, and a gene-specific dispersion, estimated by the empirical Bayes method. Last, an exact test with FDR control is used to determine DE genes.

DESeq2

DESeq2 [43] is an advanced version of DESeq [11], which is also based on the negative binomial distribution. Compared with the DESeq, which uses a fixed normalization factor, the new version of DESeq2 allows the use of a gene-specific shrinkage estimation for dispersions. When estimating the dispersion, DESeq2 uses all of the genes with a similar average expression. The fold-change estimation is also employed to avoid identifying genes with small average expression values.

DEsingle

DEsingle [36] utilizes a ZINB regression model to estimate the proportion of the real and drop-out zeros in the observed expression data. The expression values of each gene in each population of cells are estimated by a ZINB model. The probability mass function (PMF) of the ZINB model for read counts of gene g in a group of cells is:
$$ {\displaystyle \begin{array}{c}P\left({N}_g=n|\theta, r,p\right)=\theta \bullet I\left(n=0\right)+\left(1-\theta \right)\bullet {f}_{NB}\left(r,p\right)\\ {}=\theta \bullet I\left(n=0\right)+\left(1-\theta \right)\bullet \left(\begin{array}{c}n+r-1\\ {}n\end{array}\right){p}^n{\left(1-p\right)}^r\end{array}}, $$
where θ is the proportion of constant zeros of gene g in the group of cells, I(n = 0) is an indicator function, fNB is the PMF of the NB distribution, r is the size parameter and p is the probability parameter of the NB distribution. By testing the parameters (θ, r, and p) of two ZINB models for the two different groups of cells, the method can classify the DE genes into three categories: 1—different expression status (DEs), 2—differential expression abundance (DEa), and 3—general differential expression (DEg). DEs represents genes that they show significant different proportion of cells with real zeros in different groups (i.e. θs are significantly different) but the expression of these genes in the remaining cells show no significance (i.e. r, and p show no significance). DEa represents genes that they show no significance in the proportion of real zeros, but show significant differential expression in remaining cells. DEg represents genes that they not only have significant difference in the proportion of real zeros, but also significantly expressed differentially in the remaining cells.

SigEMD

SigEMD [37] employs logistic regression to identify the genes that their zero counts significantly affect the distribution of expression values; and employs Lasso regression to impute the zero counts of the identified genes. Then, for these identified genes, SigEMD employs EMD, similar to EMDomics, for differential analysis of expression values’ distributions including the zero values; while for the remaining genes, it employs EMD for differential analysis of expression values’ distributions ignoring the zero values. The regression model and data imputation declines the impact of large amounts of zero counts, and EMD enhances the sensitivity of detecting DE genes from multimodal scRNAseq data.

Datasets

In this work, we used both simulated and real data to evaluate the performance of the differential expression analysis tools.

Simulated data

As we do not know exactly the true DE genes in real single-cell data, we used simulated data to compute the sensitivities and specificities of the eleven methods. Data heterogeneity (multimodality) and sparsity (large number of zero counts), which are the main characteristics of scRNAseq data, are modeled in simulated data. First, we generated 10 datasets, including simulated read counts in the form of log-transformed counts, across a two-condition problem by employing a simulation function from the scDD package [30] in R programing language [45]. For each condition, there were 75 single cells with 20,000 genes in each cell. Among the total 20,000 genes, 2000 genes were simulated with differential distributions, and 18,000 genes were simulated as non-DE genes. The 2000 DE genes were equally divided into four groups, corresponding to the DU, DP, DM, and DB scenarios (Additional file 1: Figure S1). Examples of these four situations from the real data are shown in Fig. 1a. From the 18,000 non-DE genes, 9000 genes were generated, using a unimodal NB distribution (EE scenario), and the other 9000 genes were simulated using a bimodal distribution (EP scenario). All of the non-DE genes had the same mode across the two conditions. Then, we simulated drop-out events by introducing large numbers of zero counts. To introduce zero counts, first, we built the cumulative distribution function (CDF) of the percentage of zeros of each gene, using the real data, FX(x). Then, in the simulated data for each gene, we randomly selected c (c~ FX(x)) cells from the total cells for half of the genes in each scenario and forced their expression values to zero (10,000 genes in total). Thus, the CDF of the percentage of zeros of each gene is similar between the simulated and real data (Additional file 1: Figure S2). This way, the distribution of the total counts in the simulated data is more similar to real data, which enables us to assess the true positives (TPs) and false positives (FPs) more accurately.

Real data

We used the real scRNAseq dataset provided by Islam et al. [46] as the positive control dataset to compute TP rates. The datasets consist of 22,928 genes from 48 mouse embryonic stem cells and 44 mouse embryonic fibroblasts. The count matrix is available in the Gene Expression Omnibus (GEO) database with Accession No. GSE29087. To assess TPs, we used the already-published top 1000 DE genes that are validated through qRT-PCR experiments [47] as a gold standard gene set [21, 40, 42].

We also used the dataset from Grün et al. [48] as the negative control dataset to assess FPs. We retrieved 80 pool-and-split samples that were obtained under the same condition from the GEO database with Accession No. GSE54695. By employing random sampling from the 80 samples, we generated 10 datasets to obtain the statistical characteristics of the results. For each generated dataset, we randomly selected 40 out of the 80 cells as one group and considered the remaining 40 cells as the other group [42]. Because all of the samples are under the same condition, there should be no DE genes in these 10 datasets.

In the preprocessing of the real datasets, we filtered out genes that are not expressed in all cells (zero read counts across all cells), and we used log-transformed transcript per millions (TPM) values as the input.

Results

Accuracy of identification of DE genes

Results from simulated data

We used simulated data to compute true sensitivities and precision of the tools for detecting DE genes. The receiver operating characteristic (ROC) curves, using the simulated data, are shown in Fig. 2. As can be seen in the figure, the tools show comparable areas-under-the-curve (AUC) values.
Fig. 2

ROC curves for the eleven differential gene expression analysis tools using simulated data

The average true positive rates (TPRs, sensitivities), false positive rates (FPRs), precision, accuracy, and F1 score of the tools under the adjusted p-value of 0.05 are given in Table 2. We defined TPs as the truly called DE genes, and FPs as the genes that were called significant but were not true DE genes. Similarly, true negatives (TNs) were defined as genes that were not true DE and were not called significant, and false negatives (FNs) were defined as genes that were true DE but were not called significant. We computed TPRs as the number of TPs over the 2000 ground-truth DE genes, FPRs as the number of FPs genes over the 18,000 genes that are not differentially expressed, precision as the number of TPs over all of the detected DE genes, and accuracy as the sum of TPs and TNs over all of the 20,000 genes.
Table 2

Numbers of the detected DE genes, sensitivities, false positive rates, precisions, and accuracies of the nine tools using simulated data for an adjusted p-value or FDR of 0.05

 

Number of detected DE genes

Sensitivity

(\( \frac{\mathrm{TP}}{\mathrm{TP}+\mathrm{FN}} \))

False positive rate

(\( \frac{\mathrm{FP}}{\mathrm{FP}+\mathrm{TN}} \))

Precision

(\( \frac{\mathrm{TP}}{\mathrm{TP}+\mathrm{FP}} \))

Accuracy

(\( \frac{\mathrm{TP}+ TN}{\mathrm{P}+\mathrm{N}} \))

F1 score

(\( \frac{2 TP}{2 TP+ FP+ FN} \))

Monocle2

4664.6

0.785

0.172

0.337

0.824

0.472

EMDomics

2465.8

0.666

0.063

0.540

0.910

0.596

DESeq2

2182.6

0.739

0.039

0.677

0.939

0.707

D3E

1683.4

0.565

0.031

0.671

0.929

0.613

scDD

1155.8

0.505

0.008

0.875

0.943

0.640

MAST

954.4

0.470

0.001

0.986

0.946

0.637

edgeR

1161.2

0.557

0.003

0.959

0.953

0.705

SCDE

842

0.419

0.0003

0.994

0.942

0.590

SINCERA

633.6

0.312

0.001

0.984

0.931

0.474

DEsingle

1448.8

0.697

0.003

0.962

0.967

0.808

SigEMD

1456

0.682

0.005

0.937

0.964

0.790

As seen in Table 2, Monocle2 identified the greatest number of true DE genes but also introduced the greatest number of false DE genes, which results in a low identification accuracy, at 0.824. The nonparametric methods, EMDomics and D3E, identified more true DE genes compared to parametric methods (2465.8 and 1683.4 true DE genes, respectively). They also, however, introduced many FPs, resulting in lower accuracies (0.91 and 0.929, respectively) than did parametric methods. In contrast, tools with higher precisions, larger than 0.9 (MAST, SCDE, edgeR, and SINCERA), introduce lower numbers of FPs but identify lower numbers of TPs. Interestingly, F1 scores show that DESeq2 and edgeR, which are designed for traditional bulk RNAseq data, do not show poor performance compared to the tools that are designed for scRNAseq data. DEsingle and SigEMD performed the best in terms of accuracy and F1 score since they identified high TPs and did not introduce many FPs.

A bar plot of true detection rates of the eleven tools under the four scenarios for DE genes (i.e., DU, DM, DP, and DB) and the two scenarios for non-DE genes (i.e., EP and EE), are shown in Fig. 3. As shown in the figure, all of the methods could achieve a TPR near to or larger than 0.5 for the DU and DM scenarios, where there is no multimodality (DU scenario) or the level of multimodality is low (DM scenario). For scenarios with a high level of multimodality (DP and DB), however, some of the tools, except EMDomics, Monocle2, DESeq2, D3E, DEsingle, and SigEMD, perform poorly. In the DP scenario, only EMDomics and Monocle2 exhibited TPRs larger than 0.5, and SCDE fails for this multimodal scenario. Similarly, for the DB scenario, Monocle2, DESeq2, and DEsingle have a TPR larger than 0.5; however, MAST and SINCERA completely fail. SigEMD exhibited a TPR around 0.5 for both DP and DB scenarios. DEsingle performed the best for the DB scenario but exhibited a low TPR for the DP scenario. We showed the TPRs and true negative rates, using the simulated data with and without large numbers of zeros separately in Additional file 1: Figures S3 and S4. All of the tools have a better performance for the four scenarios when there are not large numbers of zero counts. We also showed the ROC curve for the data with and without large numbers of zeros in Additional file 1: Figures S5 and S6.
Fig. 3

True detection rates for different scenarios of DE genes and non-DE genes using simulated data. a true positive rates for DE genes under DU, DP, DM, DB scenarios b true negative genes for non-DE genes under EP and EE scenarios

It is important to notice that, even though simulated data contain multimodality and zero counts, they cannot capture the real multimodality and zero count behaviors of real data. Therefore, as seen in the following, we evaluated the detection accuracy of detecting DE genes, using real data.

Results from positive control real data

We used the positive control real dataset to evaluate the accuracy of the identification of DE genes. We employed the validated 1000 genes as a gold standard gene set. We defined true detected DE genes as DE genes that are called by the tools and are among the 1000 gold standard DE genes. The number of detected DE genes and the number of true detected DE genes over the 1000 gold standard genes (defined as sensitivity) for each tool, using an FDR or adjusted p-value of 0.05, are given in Table 3.
Table 3

Number of detected DE genes, and sensitivities of the eleven tools using positive control real data for an adjusted p-value or FDR of 0.05

 

Number of detected DE genes

Sensitivity (TP/1000 gold standard)

Monocle2

8674

0.765

EMDomics

8437

0.762

DESeq2

7612

0.695

D3E

8401

0.722

scDD

2638

0.351

MAST

734

0.198

edgeR

4447

0.58

SCDE

2414

0.392

SINCERA

8366

0.73

DEsingle

9031

0.797

SigEMD

3702

0.488

The tools can be ranked in three levels based on their sensitivities: Monocle2, EMDomics, SINCERA, D3E, and DEsingle rank in the first level, with sensitivities more than 0.7; edgeR, DESeq2, and SigEMD rank in the second level, with sensitivities between 0.4 and 0.7; and SCDE, scDD, and MAST rank in the third level with sensitivities below 0.4. The methods that show better sensitivities, however, also called more than 7000 genes as significantly DE genes. In Fig. 4, the blue bars show the intersection between the gold standard genes and the DE genes called by the methods (true detected DE genes), whereas the yellow bars show the number of significantly DE genes that are not among the gold standard genes.
Fig. 4

Tools’ total numbers of detected significantly DE genes with the p-value or FDR threshold of 0.05 and their overlaps with the 1000 gold standard genes

We need to note that we do not have all of the true positive DE genes for the positive control dataset. The 1000 gold standard genes are a subset of DE genes from the dataset that are validated through qRT-PCR experiments [47]. In addition, the datasets that we used in this study have been generated under similar conditions as those of the positive control datasets; however, they are not from the same assay and experiment. Therefore, the results we present here provide information about sensitivities to some degree.

Results in negative control real data

Because all of the real true DE genes in the positive control real dataset are unknown, we can test only the TPs, using the 1000 gold standard genes but not the FPs. To validate the FPs, we applied the methods to 10 datasets with two groups, randomly sampled from the negative control real dataset. Because cells in the two groups are from the same condition, we expect the methods to not identify any DE gene. Using an FDR or adjusted p-value of 0.05, MAST, SCDE, edgeR, and SINCERA did not call any gene as a DE gene, as we expected, whereas DEsingle, scDD, DESeq2, SigEMD, D3E, EMDomics, and Monocle2 identified 4, 5, 19, 50, 160, 733, and 917 significantly DE genes, respectively, out of 7277 genes in average over the 10 datasets. The number of detected DE genes and FPRs are shown in Table 4. EMDomics and Monocle2, which show the best sensitivities, using the positive control datasets, introduce the most FPs.
Table 4

Number of the detected DE genes and false positive rates of the eleven tools using negative control real data for an adjusted p-value or FDR of 0.05

 

Number of detected DE genes

False positive rate (FP/FP + TN)

Monocle2

917

0.126

EMDomics

733

0.101

DESeq2

19

0.003

D3E

160

0.022

scDD

5

0.0007

MAST

0

0

edgeR

0

0

SCDE

0

0

SINCERA

0

0

DEsingle

4

0.0005

SigEMD

50

0.007

Agreement among the methods in identifying DE genes

In general, agreement among all of the tools is very low. Considering the top 1000 DE genes detected by the eleven tools in the positive control real data, there are only 92 common DE genes across all of the tools. Of these 92 DE genes, only 41 intersect with the gold standard 1000 DE genes.

We investigated how much the tools agreed with each other on identifying DE genes by examining the number of identified DE genes that were common across a pair of tools, which we called common DE genes. First, we ranked genes by their adjusted p-values or FDRs, and then we selected the top 1000 DE genes. We defined pairwise agreement as the number of common DE genes identified by a pair of tools. The numbers of common DE genes between pairs of tools are between 770 and 1753 for simulated data (Additional file 1: Figure S7), and 142 and 856 for real data (Fig. 5). We observed that the methods do not have high pairwise agreement in either the simulated data or the real data.
Fig. 5

Numbers of pairwise common DE genes tested by top 1000 genes in real data

In addition, we used significantly DE genes under a p-value or FDR threshold of 0.05 to investigate the pairwise agreement among the tools. The pairwise agreement varies from 432 to 7934 for the real data (Fig. 6) and from 444.8 to 1878 for the simulated data (Additional file 1: Figure S8). In the real data, MAST identified fewer significantly DE genes under the 0.05 cut-off adjusted p-value, but the majority of its significantly DE genes overlapped with the significantly DE genes from other tools.
Fig. 6

Numbers of pairwise common DE genes tested by adjusted p-value< 0.05 in real data

Effect of sample size

We investigated the effect of sample size on detecting DE genes in terms of TPR, FPR, precision, and accuracy, using the simulated data. Precision was defined as TP/(TP + FP) and accuracy as (TP + TN)/(TP + TN + FP + FN). We generated eight cases: 10 cells, 30 cells, 50 cells, 75 cells, 100 cells, 200 cells, 300 cells, and 400 cells for each condition. We noticed that the number of identified DE genes and the TPRs of detection under a default FDR or adjusted p-value (< 0.05) tend to increase when the sample size increases from 10 to 400 (Fig. 7) for all tools.
Fig. 7

Effect of sample size (number of cells) on detecting DE genes. The sample size is in horizontal axis, from 10 to 400 cells in each condition. Effect of sample size on a TPR, b FPR, c accuracy (=(TP + TN)/(TP + FP + TN + FN)), and precision (=TP/(TP + FP)). A threshold of 0.05 is used for FDR or adjusted p-value

The results show that sample size is very important, as the tools’ precision increases significantly by increasing the sample size from 10 to 75. The FPRs tend to be steady when the sample size is > 75, except for DEsingle. DEsingle works well for a large number of zero counts in a larger dataset. These results also show that Monocle2, EMDomics, DESeq2, DEsingle, and SigEMD can achieve TPRs near 100% by increasing the sample size, while the other methods cannot. Monocle2, EMDomics, DESeq2, and D3E, however, introduce FPs (FPR > 0.05%), whereas FPRs for other methods are very low (close to zero). All of the tools similarly perform poorly for a sample size of < 30. When the sample size exceeded 75 in each condition, the tools achieved better accuracy in detection.

Enrichment analysis of real data

To examine whether the identified DE genes are meaningful to biological processes, we conducted gene set enrichment analysis through the “Investigate Gene Sets” function of the web-based GSEA software tool (http://www.broadinstitute.org/gsea/msigdb/annotate.js). We investigated the KEGG GENES database (KEGG; contains 186 gene sets) from the Molecular Signatures Database (MSigDB) for the gene set enrichment analysis (FDR threshold of 0.05). We used the same number of identified DE genes (top n = 300 genes) of each tool as the input for KEGG pathway enrichment analysis. The results are shown in Table 5. We observed that the 300 top-ranked DE genes identified by nonparametric methods (EMDomics and D3E) were enriched for more KEGG pathways compared to other methods. We also used a box plot to compare the FDRs of the top 10 most significant gene sets enriched by the top-ranked DE genes from the tools (Additional file 1: Figure S9). It can be observed that pathways enriched by the top-ranked DE genes from edgeR and Monocle2 have the highest strength. The 10 top-ranked KEGG pathways for the eleven tools are listed in Additional file 1: Tables S1 to S11.
Table 5

Number of KEGG gene sets and GO terms enriched by the top 300 DE genes identified by each tool under an FDR threshold of 0.05

Methods

KEGG

GO Term

EMDomics

53

19

MAST

10

5

D3E

49

10

SCDE

21

9

Monocle2

42

24

SINCERA

39

16

scDD

26

1

DESeq2

39

19

edgeR

39

17

SigEMD

23

15

DEsingle

41

21

We also used DAVID (https://david.ncifcrf.gov/summary.jsp) for the Gene Ontology Process enrichment analysis of the 300 top-ranked DE genes identified by each tool. The numbers of gene ontology (GO) terms under a cutoff FDR of 0.05 are shown in Table 5. Top DE genes identified by EMDomics, D3E, Monocle, and DESeq2 are enriched in more KEGG pathways and/or GO terms compared to those of other tools.

Finally, although the quantitative values of terms recovered from gene set enrichment analysis is informative with regard to the relative statistical power of calling biologically meaningful genes of these tools, very different gene lists can result in very similar quantitative performance values. To perform a qualitative assessment of the biological relevance of the differentially expressed gene lists recovered by each tool, we ranked the performance of each tool in recovering stem cell-relevant GO terms from the 300 top-ranked DE genes. Each gene list was subjected to gene set enrichment against the Biological Process portion of the Gene Ontology Process, and all significant enriched terms were recovered. The results of the Gene Ontology Process enrichment analysis of the 300 top-ranked DE genes and the list of the 300 top-ranked genes for each tool are given in Additional file 2. Significant GO terms with their negative log transform of their q-values for each tool are given in Additional file 3. To consolidate closely related processes recovered in this step, we subjected each list of GO terms to word and phrase significance analysis, using world cloud analysis, whereby negative log transform q-values are considered as frequencies in this analysis. The phrase significance of each tool, in the form of word clouds, is shown in Additional file 1: Figures S10–S20, and the word significance, in the form of word clouds, is shown in Additional file 1: Figures S21–S31. In these plots, the font size represents the significance of the word/phrase. This provides a readily interpretable visualization of the biologically relevant GO terms.

Several stem cell biologists were then asked to rank the performance of each algorithm in terms of its ability to recover the GO terms most relevant to the experiment that provides the real dataset used in this study. Each algorithm was scored on a 1–3 scale, with 3 as the best recovery of biologically relevant terms and phrases; then, the scores for terms and phrases were added to give an overall performance score from 2 to 6 (Table 6). As expected, many of these tools recovered, at high significance, several terms strongly related to stem cell biology, including development, differentiation, morphogenesis, multicellular, and adhesion as well as many others. Interestingly, scDD and SCDE failed to recover stem cell-relevant terms at high significance. Instead, these approaches appeared to yield terms and phrases related to cellular housekeeping processes. Monocle2 and MAST performed the best at recovering stem cell-relevant terms. Following them, EMDomics, DESeq2, D3E, DEsingle, SigEMD, edgeR, SINCERA all performed well. This result strongly suggests not only that the methods used for identifying DE genes may yield non-overlapping and quantitatively different gene sets but that some methods are much better at extracting biologically relevant gene sets from the data.
Table 6

Scores from word and phrase significance analysis of each tool to recover biologically relevant terms and phrases

Methods

Score (phrase)

Score (word)

Overall score (word+phrase)

Monocle2

3

3

6

MAST

3

3

6

DESeq2

2

3

5

D3E

2

3

5

DEsingle

2

3

5

SigEMD

3

2

5

EMDomics

2

2

4

edgeR

2

2

4

SINCERA

2

2

4

SCDE

1

1

2

scDD

1

1

2

Runtimes

We compared the runtimes of the eleven tools (Table 7). Except for D3E, which was implemented in Python, all of the tools were implemented in R (Table 1). The runtime was computed using a personal computer, iMac with 3.1GHz CPU and up to 8 gigabytes of memory. The average runtime (of 10 times) of each tool, using the positive control dataset, is shown in Table 7. SINCERA has the lowest time cost because it employs a simple t-test. edgeR has the lowest time cost among the model-based and nonparametric methods. MAST, Monocle2, and DESeq2 run fast (less than 5 min), as MAST and Monocle2 use linear regression methods, and DESeq2 uses a binomial model for identifying DE genes. scDD takes longer, as it needs time to classify DE genes into different modalities. The nonparametric method, SigEMD, EMDomics and D3E, take more time compared to the model-based methods because they need to compute the distance between two distributions for each gene. We note that D3E had two running modes: It takes about 40 min when running under the simple mode and about 30 h when running under the more accurate mode.
Table 7

Average runtime of identifying DE genes in real data by each tool

Methods

Platform

Time consumption in minutes

DESeq2

R

4.2

edgeR

R

0.41

scDD

R

85.13

EMDomics

R

14.64

MAST

R

1.47

D3E

Python

38.43

Monocle2

R

2.6

SCDE

R

10.39

SINCERA

R

0.3

DEsingle

R

14.97

SigEMD

R

14.86

Discussion

As shown in Fig. 1, scRNAseq expression data are multimodal, with a high number of zero counts that make differential expression analysis challenging. In this study, we conducted a comprehensive evaluation of the performance of eleven software tools for single cell differential gene expression analysis: SCDE, MAST, scDD, EMDomics, D3E, Monocle2, SINCERA, edgeR, DESeq2, DEsingle, and SigEMD. Using simulated data and real scRNAseq data, we compared the accuracy of the tools in identifying DE genes, agreement among the tools in detecting DE genes, and time consumption of the tools. We also examined the enrichment of the identified DE genes by running pathway analysis and GO analysis for the real data.

Detection accuracy

In general, the eleven methods behave differently in terms of calling true significantly DE genes. The tools that show higher sensitivity also show lower precision. Among all of the tools, DEsingle and SigEMD, which are designed for the scRNAseq, tend to show a better trade-off between TPRs and precision.

All of the tools perform well when there is no multimodality or low levels of multimodality. They all also perform better when the sparsity (zero counts) is less. For data with a high level of multimodality, methods that consider the behavior of each individual gene, such as DESeq2, EMDomics, Monocle2, DEsingle, and SigEMD, show better TPRs. This is because EMDomics and SigEMD use a nonparametric method to compute the distance between two distributions and can capture the multimodality; DEsingle models dropout events well by using a zero inflated negative model to estimate the proportion of real and drop-out zeros in the expression value; Monocle2 uses a census algorithm to estimate the relative transcript counts for each gene instead of using normalized read counts, such as TPM values; and DESeq2 uses a gene-specific shrinkage estimation for the dispersions parameter to fit a negative binomial model to the read counts. If the level of multimodality is low, however, SCDE, MAST, and edgeR can provide higher precision.

Agreement among the methods

The overall agreement in terms of finding DE genes among all of the tools is low. We used the top 1000 DE genes identified by the eleven tools (ranked by p-values) and significantly DE genes with a significant threshold of 0.05 to identify the common DE genes across the tools and between pairs of tools. The DE genes identified by DESeq2, EMDomics, D3E, Monocle2, SINCERA, DEsingle, and SigEMD show higher pairwise agreement, whereas the model-based methods, SCDE and scDD, show less pairwise agreement within other tools. No single tool is clearly superior for identifying DE genes, using single cell sequencing datasets. The tools use different methods with different strengths and limitations for calling DE genes. The sequencing data also are very noisy. The methods treat zero counts, multimodality, and noise differently, resulting in low agreement among them. Some tools work well when the drop-out event is not significant and some, when data multimodality is not significant. For instance, scDD aims at characterizing different patterns of differential distributions; however, handling a large number of zero counts in the expression values is a challenging task for this tool.

Sample size effect

All of the tools perform better when there are more samples in each condition. TPRs improve significantly by increasing sample size from 10 to 75, but they slow down for sample sizes greater than 100; and for sample sizes of 300 and larger, there are almost no changes in TPRs and FPRs. Monocle2, EMDomics, DESeq2, DEsingle, and SigEMD can achieve a TPR close to 100% by increasing the sample size. DEsingle works well for a larger number of zero counts or small number of samples. When the number of zero counts is low and the number of samples is large, its model cannot capture the dropout event well.

Enrichment analysis

As expected, top-ranked DE genes of many of these tools are enriched for GO terms strongly related to stem cell biology. scDD and SCDE, however, failed to recover stem cell-relevant terms at high significance. Instead, they appeared to yield GO terms related to cellular housekeeping processes. This result suggests that model-based single cell DE analysis methods that do not consider multimodality do not perform well in extracting biologically relevant gene sets from the data.

Conclusion

In conclusion, the identification of DE genes, using scRNAseq data, remains challenging. Tools developed for scRNAseq data focus on handling zero counts or multimodality but not both. In general, the methods that can capture multimodality (non-parametric methods), perform better than do the model-based methods designed for handling zero counts. However, a model-based method that can model the drop-out events well, can perform better in terms of true positive and false positive. We observed that methods developed specifically for scRNAseq data do not show significantly better performance compared to the methods designed for bulk RNAseq data; and methods that consider behavior of each individual gene (not all genes) in calling DE genes outperform the other tools. The lack of agreement in finding DE genes by these tools and their limitations in detecting true DE genes and biologically relevant gene sets indicate the need for developing more precise methods for differential expression analysis of scRNAseq data. Multimodality, heterogeneity, and sparsity (many zero counts) are the main characteristics of scRNAseq data that all need to be addressed when developing new methods.

Notes

Acknowledgments

Not applicable.

Funding

This study was supported by a grant from the National Institutes of Health (NIH, R00LM011595, PI: Nabavi).

Availability of data and materials

The single cell RNAseq data are publicly available in Gene Expression Omnibus, accession number GSE29087 and GSE54695.

Authors’ contributions

SN and TW designed the study. TW, BL, and CN implemented the analysis. SN, CN and TW wrote the manuscript. All authors read and approved the final manuscript.

Ethics approval and consent to participate

No ethics approval was required for the study.

Consent for publication

Not applicable.

Competing interests

The authors declare that they have no competing interests.

Publisher’s Note

Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.

Supplementary material

12859_2019_2599_MOESM1_ESM.docx (2.2 mb)
Additional file 1: Supplementary materials (Supplementary Tables S1-S11, Supplementary Figures S1-S31). (DOCX 2225 kb)
12859_2019_2599_MOESM2_ESM.xlsx (116 kb)
Additional file 2: Results of the Gene Ontology Process enrichment analysis of the 300 top-ranked DE genes and the list of the 300 top-ranked genes for each tool. (XLSX 115 kb)
12859_2019_2599_MOESM3_ESM.csv (25 kb)
Additional file 3: Significant GO terms with their negative log transform of their q-values for each tool. (CSV 24 kb)

References

  1. 1.
    Metzker ML. Sequencing technologies — the next generation. Nat Rev Genet. 2010;11:31–46.CrossRefGoogle Scholar
  2. 2.
    Perry GH, Melsted P, Marioni JC, Wang Y, Bainer R, Pickrell JK, et al. Comparative RNA sequencing reveals substantial genetic variation in endangered primates. Genome Res. 2012;22:602–10.CrossRefGoogle Scholar
  3. 3.
    Arnold CD, Gerlach D, Stelzer C, Boryń ŁM, Rath M, Stark A. Genome-wide quantitative enhancer activity maps identified by STARR-seq. Science. 2013;339:1074–7.CrossRefGoogle Scholar
  4. 4.
    Han Y, Gao S, Muegge K, Zhang W, Zhou B. Advanced applications of RNA sequencing and challenges. Bioinforma Biol Insights. 2015;9(Suppl 1):29–46.Google Scholar
  5. 5.
    Schissler AG, Li Q, Chen JL, Kenost C, Achour I, Billheimer DD, et al. Analysis of aggregated cell–cell statistical distances within pathways unveils therapeutic-resistance mechanisms in circulating tumor cells. Bioinformatics. 2016;32:i80–9.CrossRefGoogle Scholar
  6. 6.
    Saliba A-E, Westermann AJ, Gorski SA, Vogel J. Single-cell RNA-seq: advances and future challenges. Nucleic Acids Res. 2014;42:8845–60.CrossRefGoogle Scholar
  7. 7.
    Stegle O, Teichmann SA, Marioni JC. Computational and analytical challenges in single-cell transcriptomics. Nat Rev Genet. 2015;16:133–45.CrossRefGoogle Scholar
  8. 8.
    Bacher R, Kendziorski C. Design and computational analysis of single-cell RNA-sequencing experiments. Genome Biol. 2016;17.  https://doi.org/10.1186/s13059-016-0927-y.
  9. 9.
    Grün D, van Oudenaarden A. Design and analysis of single-cell sequencing experiments. Cell. 2015;163:799–810.CrossRefGoogle Scholar
  10. 10.
    Myers JS, von Lersner AK, Robbins CJ, Sang Q-XA. Differentially expressed genes and signature pathways of human prostate Cancer. PLoS One. 2015;10:e0145322.CrossRefGoogle Scholar
  11. 11.
    Anders S, Huber W. Differential expression analysis for sequence count data. Genome Biol. 2010;11:R106.CrossRefGoogle Scholar
  12. 12.
    Robinson MD, McCarthy DJ, Smyth GK. edgeR: a Bioconductor package for differential expression analysis of digital gene expression data. Bioinformatics. 2010;26:139–40.CrossRefGoogle Scholar
  13. 13.
    Leng N, Dawson JA, Thomson JA, Ruotti V, Rissman AI, Smits BMG, et al. EBSeq: an empirical Bayes hierarchical model for inference in RNA-seq experiments. Bioinformatics. 2013;29:1035–43.CrossRefGoogle Scholar
  14. 14.
    Hardcastle TJ, Kelly KA. baySeq: empirical Bayesian methods for identifying differential expression in sequence count data. BMC Bioinformatics. 2010;11:422.CrossRefGoogle Scholar
  15. 15.
    Di Y, Schafer DW, Cumbie JS, Chang JH. The NBP negative binomial model for assessing differential gene expression from RNA-Seq. Stat Appl Genet Mol Biol. 2011;10.  https://doi.org/10.2202/1544-6115.1637.
  16. 16.
    Smyth GK. Linear models and empirical bayes methods for assessing differential expression in microarray experiments. Stat Appl Genet Mol Biol. 2004;3:Article3.CrossRefGoogle Scholar
  17. 17.
    Ritchie ME, Phipson B, Wu D, Hu Y, Law CW, Shi W, et al. Limma powers differential expression analyses for RNA-sequencing and microarray studies. Nucleic Acids Res. 2015;43:e47.CrossRefGoogle Scholar
  18. 18.
    Li J, Tibshirani R. Finding consistent patterns: a nonparametric approach for identifying differential expression in RNA-Seq data. Stat Methods Med Res. 2013;22:519–36.CrossRefGoogle Scholar
  19. 19.
    Tarazona S, García-Alcalde F, Dopazo J, Ferrer A, Conesa A. Differential expression in RNA-seq: a matter of depth. Genome Res. 2011;21:2213–23.CrossRefGoogle Scholar
  20. 20.
    Auer PL, Doerge RW. A two-stage Poisson model for testing RNA-Seq data. Stat Appl Genet Mol Biol. 2011;10.  https://doi.org/10.2202/1544-6115.1627.
  21. 21.
    Kharchenko PV, Silberstein L, Scadden DT. Bayesian approach to single-cell differential expression analysis. Nat Methods. 2014;11:740–2.CrossRefGoogle Scholar
  22. 22.
    Elowitz MB, Levine AJ, Siggia ED, Swain PS. Stochastic gene expression in a single cell. Science. 2002;297:1183–6.CrossRefGoogle Scholar
  23. 23.
    Raj A, van Oudenaarden A. Stochastic gene expression and its consequences. Cell. 2008;135:216–26.CrossRefGoogle Scholar
  24. 24.
    Patel AP, Tirosh I, Trombetta JJ, Shalek AK, Gillespie SM, Wakimoto H, et al. Single-cell RNA-seq highlights intratumoral heterogeneity in primary glioblastoma. Science. 2014;344:1396–401.CrossRefGoogle Scholar
  25. 25.
    Darmanis S, Sloan SA, Zhang Y, Enge M, Caneda C, Shuer LM, et al. A survey of human brain transcriptome diversity at the single cell level. Proc Natl Acad Sci U S A. 2015;112:7285–90.CrossRefGoogle Scholar
  26. 26.
    Steinmeyer JD, Yanik MF. High-throughput single-cell manipulation in brain tissue. PLoS One. 2012;7:e35603.CrossRefGoogle Scholar
  27. 27.
    Tirosh I, Izar B, Prakadan SM, Wadsworth MH, Treacy D, Trombetta JJ, et al. Dissecting the multicellular ecosystem of metastatic melanoma by single-cell RNA-seq. Science. 2016;352:189–96.CrossRefGoogle Scholar
  28. 28.
    Nelson SB. Cortical microcircuits: diverse or canonical? Neuron. 2002;36:19–27.CrossRefGoogle Scholar
  29. 29.
    Finak G, McDavid A, Yajima M, Deng J, Gersuk V, Shalek AK, et al. MAST: a flexible statistical framework for assessing transcriptional changes and characterizing heterogeneity in single-cell RNA sequencing data. Genome Biol. 2015;16.  https://doi.org/10.1186/s13059-015-0844-5.
  30. 30.
    Korthauer KD, Chu L-F, Newton MA, Li Y, Thomson J, Stewart R, et al. scDD: a statistical approach for identifying differential distributions in single-cell RNA-seq experiments. bioRxiv. 2016:035501.  https://doi.org/10.1101/035501.
  31. 31.
    Nabavi S, Schmolze D, Maitituoheti M, Malladi S, Beck AH. EMDomics: a robust and powerful method for the identification of genes differentially expressed between heterogeneous classes. Bioinformatics. 2016;32:533–41.CrossRefGoogle Scholar
  32. 32.
    Trapnell C, Cacchiarelli D, Grimsby J, Pokharel P, Li S, Morse M, et al. The dynamics and regulators of cell fate decisions are revealed by pseudotemporal ordering of single cells. Nat Biotechnol. 2014;32:381–6.CrossRefGoogle Scholar
  33. 33.
    Delmans M, Hemberg M. Discrete distributional differential expression (D3E) - a tool for gene expression analysis of single-cell RNA-seq data. BMC Bioinformatics. 2016;17:110.CrossRefGoogle Scholar
  34. 34.
    Guo M, Wang H, Potter SS, Whitsett JA, Xu Y. SINCERA: a pipeline for single-cell RNA-Seq profiling analysis. PLoS Comput Biol. 2015;11:e1004575.CrossRefGoogle Scholar
  35. 35.
    Katayama S, Töhönen V, Linnarsson S, Kere J. SAMstrt: statistical test for differential expression in single-cell transcriptome with spike-in normalization. Bioinformatics. 2013;29:2943–5.CrossRefGoogle Scholar
  36. 36.
    Miao Z, Deng K, Wang X, Zhang X. DEsingle for detecting three types of differential expression in single-cell RNA-seq data. Bioinformatics. 2018;34:3223–4.CrossRefGoogle Scholar
  37. 37.
    Wang T, Nabavi S. SigEMD: a powerful method for differential gene expression analysis in single-cell RNA sequencing data. Methods San Diego Calif. 2018;145:25–32.CrossRefGoogle Scholar
  38. 38.
    Qiu X, Hill A, Packer J, Lin D, Ma Y-A, Trapnell C. Single-cell mRNA quantification and differential analysis with census. Nat Methods 2017;advance online publication. doi: https://doi.org/10.1038/nmeth.4150.
  39. 39.
    Korthauer KD, Chu L-F, Newton MA, Li Y, Thomson J, Stewart R, et al. A statistical approach for identifying differential distributions in single-cell RNA-seq experiments. Genome Biol. 2016;17.  https://doi.org/10.1186/s13059-016-1077-y.
  40. 40.
    Jaakkola MK, Seyednasrollah F, Mehmood A, Elo LL. Comparison of methods to detect differentially expressed genes between single-cell populations. Brief Bioinform.  https://doi.org/10.1093/bib/bbw057.
  41. 41.
    Miao Z, Zhang X. Differential expression analyses for single-cell RNA-Seq: old questions on new data. Quant Biol. 2016;4:243–60.CrossRefGoogle Scholar
  42. 42.
    Dal Molin A, Baruzzo G, Di Camillo B. Single-cell RNA-sequencing: assessment of differential expression analysis methods. Front Genet. 2017;8.  https://doi.org/10.3389/fgene.2017.00062.
  43. 43.
    Love MI, Huber W, Anders S. Moderated estimation of fold change and dispersion for RNA-seq data with DESeq2. Genome Biol. 2014;15:550.CrossRefGoogle Scholar
  44. 44.
    Benjamini Y, Hochberg Y. Controlling the false discovery rate: a practical and powerful approach to multiple testing. J R Stat Soc Ser B Methodol. 1995;57:289–300.Google Scholar
  45. 45.
    R Core Team. R: a language and environment for statistical computing. Vienna: R Foundation for Statistical Computing; 2016. URL https://www.R-project.org/ . https://www.R-project.org/ Google Scholar
  46. 46.
    Islam S, Kjällquist U, Moliner A, Zajac P, Fan J-B, Lönnerberg P, et al. Characterization of the single-cell transcriptional landscape by highly multiplex RNA-seq. Genome Res. 2011;21:1160–7.CrossRefGoogle Scholar
  47. 47.
    Moliner A, Enfors P, Ibáñez CF, Andäng M. Mouse embryonic stem cell-derived spheres with distinct neurogenic potentials. Stem Cells Dev. 2008;17:233–43.CrossRefGoogle Scholar
  48. 48.
    Grün D, Kester L, van Oudenaarden A. Validation of noise models for single-cell transcriptomics. Nat Methods. 2014;11:637–40.CrossRefGoogle Scholar

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© The Author(s). 2019

Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.

Authors and Affiliations

  1. 1.Computer Science and Engineering DepartmentUniversity of ConnecticutStorrsUSA
  2. 2.Department of Molecular & Cell BiologyUniversity of ConnecticutStorrsUSA
  3. 3.Department of Molecular & Cell BiologyThe Institute for Systems Genomics, CLAS, University of ConnecticutStorrsUSA
  4. 4.Computer Science and Engineering DepartmentThe Institute for Systems Genomics, University of ConnecticutStorrsUSA

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