Bio Methylation Differential Cpg

Version Compatibility

Reference examples tested with: scipy 1.12+, statsmodels 0.14+, pandas 2.2+, numpy 1.26+, limma 3.58+, DSS 2.50+

Before using code patterns, verify installed versions match. If versions differ:

• Python: pip show <package> then help(module.function) to check signatures
• R: packageVersion('<pkg>') then ?function_name to verify parameters

If code throws ImportError, AttributeError, or TypeError, introspect the installed package and adapt the example to match the actual API rather than retrying.

Per-CpG Differential Methylation Testing

"Test individual CpG sites for differential methylation between groups" -> Compute per-CpG methylation metrics from count data, apply coverage filters, run statistical tests for group differences, correct for multiple testing, and report effect sizes.

• Python: scipy.stats.ttest_ind() + statsmodels.stats.multitest.multipletests()
• R: limma::lmFit() + eBayes() on M-values, DSS::DMLtest() on counts

Beta Values and M-Values

Goal: Convert raw bisulfite sequencing count data into analyzable methylation metrics.

Approach: Compute beta values (methylation proportion) for biological interpretation and M-values (logit-transformed) for statistical testing. Beta values are bounded [0, 1] and heteroscedastic (variance depends on methylation level). M-values are approximately homoscedastic, making them better suited for parametric tests (Du et al. 2010).

import numpy as np
import pandas as pd

# Beta value: proportion of methylated reads
# Range [0, 1], directly interpretable as methylation percentage
beta = meth_counts / total_counts

# M-value: logit transform of beta (log2 scale)
# Range (-inf, +inf), homoscedastic, better for statistical testing
# Add offset to avoid log(0) and division by zero
OFFSET = 1e-6
m_value = np.log2((beta + OFFSET) / (1 - beta + OFFSET))

# Beta value from counts
beta <- meth_counts / total_counts

# M-value: logit transform (base 2)
# Add offset to handle beta = 0 or beta = 1
offset <- 1e-6
m_value <- log2((beta + offset) / (1 - beta + offset))

# Convert M-value back to beta for reporting
# beta = 2^M / (2^M + 1)
beta_from_m <- 2^m_value / (2^m_value + 1)

When to use each metric:

• Large n (>10/group), t-test or Mann-Whitney: Testing on beta values directly is standard and acceptable. Heteroscedasticity has minimal impact with sufficient samples.
• Small n (3-5/group), limma: Convert to M-values for statistical testing. Empirical Bayes moderation on M-values produces better-calibrated p-values.
• Reporting: Always report delta_beta (difference in mean beta values) for biological interpretation regardless of which metric was used for testing.

Coverage Filtering

Goal: Remove CpGs with unreliable methylation estimates due to insufficient or artificially inflated read coverage.

Approach: Apply a minimum coverage threshold to ensure adequate resolution, and an upper percentile filter to remove PCR amplification artifacts.

# Minimum 10x: provides 11 possible methylation levels (0/10 through 10/10)
# and adequate power for statistical testing
MIN_COVERAGE = 10

# Upper 99.9th percentile: removes sites with inflated coverage from
# PCR duplication or mapping artifacts in repetitive regions
upper_threshold = np.percentile(total_counts.values.flatten(), 99.9)

# Require minimum coverage in ALL samples (any low-coverage sample
# makes that CpG unreliable for group comparison)
passes_min = (total_counts >= MIN_COVERAGE).all(axis=1)
passes_max = (total_counts <= upper_threshold).all(axis=1)
filtered = beta[passes_min & passes_max]

# Equivalent in R (without methylKit)
min_coverage <- 10
upper_threshold <- quantile(as.matrix(total_counts), 0.999)
keep <- apply(total_counts, 1, function(x) all(x >= min_coverage & x <= upper_threshold))
filtered_beta <- beta[keep, ]

Coverage Thresholds by Assay

Method Selection

Fisher's exact test on counts should be avoided when biological replicates exist. Pooling counts across replicates and testing with Fisher's inflates false positive rates to ~33% because biological variation is ignored.

Fisher's Exact Test (Python, Unreplicated Only)

from scipy.stats import fisher_exact

# Only for unreplicated designs (1 sample per group)
# table: [[meth_case, unmeth_case], [meth_ctrl, unmeth_ctrl]]
table = [[meth_case, total_case - meth_case],
         [meth_ctrl, total_ctrl - meth_ctrl]]
result = fisher_exact(table, alternative='two-sided')
# result.statistic = odds ratio, result.pvalue = p-value

Welch's t-Test on Beta Values (Python)

Goal: Test each CpG for a mean methylation difference between two groups using a parametric test that does not assume equal variances.

Approach: Compute beta values per CpG per sample, run a Welch t-test per CpG across groups, collect p-values, and apply Benjamini-Hochberg FDR correction.

import numpy as np
import pandas as pd
from scipy import stats
from statsmodels.stats.multitest import multipletests

# Assume: case_betas and ctrl_betas are DataFrames
# Rows = CpGs, columns = samples within each group
pvalues = []
for cpg_idx in range(len(case_betas)):
    case_vals = case_betas.iloc[cpg_idx].values
    ctrl_vals = ctrl_betas.iloc[cpg_idx].values
    # equal_var=False: Welch's t-test (does NOT assume equal variance)
    # scipy defaults to equal_var=True (Student's), which is almost never appropriate
    result = stats.ttest_ind(case_vals, ctrl_vals, equal_var=False, nan_policy='omit')
    pvalues.append(result.pvalue)

pvalues = np.array(pvalues)

# Benjamini-Hochberg FDR correction
# CRITICAL: multipletests defaults to method='hs' (Holm-Sidak), NOT BH
# Must explicitly pass method='fdr_bh'
reject, padj, _, _ = multipletests(pvalues, alpha=0.05, method='fdr_bh')

For large datasets, vectorized computation avoids the per-CpG loop:

from scipy.stats import ttest_ind

# Vectorized across all CpGs at once (axis=1 tests across samples)
t_stats, pvalues = ttest_ind(case_betas.values, ctrl_betas.values,
                              axis=1, equal_var=False, nan_policy='omit')

reject, padj, _, _ = multipletests(pvalues, alpha=0.05, method='fdr_bh')

Mann-Whitney U Test (Python)

Goal: Non-parametric alternative when beta-value distributions are non-normal or sample sizes are very unequal.

Approach: Per-CpG rank-based test with BH correction. No distributional assumptions, but lower power than t-test for small n.

from scipy.stats import mannwhitneyu

pvalues = []
for cpg_idx in range(len(case_betas)):
    case_vals = case_betas.iloc[cpg_idx].dropna().values
    ctrl_vals = ctrl_betas.iloc[cpg_idx].dropna().values
    # Cannot reach p < 0.05 with n < 4 per group (insufficient ranks)
    if len(case_vals) < 4 or len(ctrl_vals) < 4:
        pvalues.append(np.nan)
        continue
    result = mannwhitneyu(case_vals, ctrl_vals, alternative='two-sided')
    pvalues.append(result.pvalue)

pvalues = np.array(pvalues)
valid = ~np.isnan(pvalues)
padj = np.full_like(pvalues, np.nan)
padj[valid] = multipletests(pvalues[valid], method='fdr_bh')[1]

limma on M-Values (R)

Goal: Identify differentially methylated CpGs with small sample sizes by borrowing variance information across CpGs via empirical Bayes moderation.

Approach: Convert beta values to M-values, fit a linear model per CpG with limma, apply empirical Bayes variance shrinkage, and extract moderated test statistics. This adds ~10-20 effective degrees of freedom even with n=3 per group.

library(limma)

# M-value matrix: rows = CpGs, columns = samples
offset <- 1e-6
m_values <- log2((beta_matrix + offset) / (1 - beta_matrix + offset))

# Design matrix
group <- factor(c(rep('case', n_case), rep('ctrl', n_ctrl)))
design <- model.matrix(~ 0 + group)
colnames(design) <- levels(group)

# Contrast: case vs control
contrast_matrix <- makeContrasts(case - ctrl, levels = design)

# Fit linear model and apply empirical Bayes
fit <- lmFit(m_values, design)
fit2 <- contrasts.fit(fit, contrast_matrix)
# trend=TRUE: intensity-dependent prior variance (recommended for methylation)
# robust=TRUE: protects against outlier CpGs
fit2 <- eBayes(fit2, trend = TRUE, robust = TRUE)

# Extract results (all CpGs, BH-adjusted)
results <- topTable(fit2, number = Inf, adjust.method = 'BH', sort.by = 'none')
# Columns: logFC (on M-value scale), AveExpr, t, P.Value, adj.P.Val, B

# Convert logFC (M-value scale) back to approximate delta_beta for reporting
# For CpGs in the middle range (beta 0.2-0.8), delta_beta ~ 0.15 * logFC
# For precise delta_beta, compute from original beta values instead
delta_beta <- rowMeans(beta_matrix[, group == 'case']) -
              rowMeans(beta_matrix[, group == 'ctrl'])
results$delta_beta <- delta_beta

DSS Beta-Binomial Model (R)

Goal: Statistically principled count-based differential methylation testing that models both biological variation (Beta distribution across replicates) and sampling noise (Binomial distribution from read counts).

Approach: DSS uses a hierarchical beta-binomial model with Bayesian shrinkage for dispersion estimation. It operates directly on methylated/total count data without requiring beta or M-value conversion.

library(DSS)

# Create BSseq object from count matrices
# meth_counts: matrix of methylated read counts (CpGs x samples)
# total_counts: matrix of total read counts (CpGs x samples)
bs_obj <- BSseq(chr = cpg_chr, pos = cpg_pos,
                M = meth_counts, Cov = total_counts,
                sampleNames = sample_names)

# Define groups
group_case <- sample_names[1:n_case]
group_ctrl <- sample_names[(n_case + 1):(n_case + n_ctrl)]

# Test for differential methylation (per CpG)
# smoothing=FALSE: test individual CpGs without spatial smoothing
# smoothing=TRUE: borrows information from nearby CpGs (500bp default window)
dml_test <- DMLtest(bs_obj, group1 = group_case, group2 = group_ctrl, smoothing = FALSE)

# Extract significant DMCs
# p.threshold: FDR-adjusted p-value cutoff
dmcs <- callDML(dml_test, p.threshold = 0.05)

Effect Size Calculation

Goal: Quantify the magnitude of methylation difference at each CpG for biological interpretation and downstream filtering.

Approach: Compute delta_beta as the difference in mean beta values between groups. Apply effect size thresholds appropriate to the biological context.

delta_beta = case_betas.mean(axis=1).values - ctrl_betas.mean(axis=1).values

delta_beta <- rowMeans(beta_matrix[, group == 'case']) -
              rowMeans(beta_matrix[, group == 'ctrl'])

Effect Size Thresholds

The appropriate threshold depends on biological context. Promoter CpG islands are often bimodal (either <10% or >80% methylated), so even small changes near the transition boundary can be functionally meaningful.

methylKit's meth.diff is derived from its logistic regression model and is not identical to mean(case_beta) - mean(ctrl_beta). When comparing results across tools, always recompute delta_beta from the original beta values for consistency.

Full Python Pipeline

Goal: Complete per-CpG differential methylation analysis from a count-data TSV through to a results table with statistics and effect sizes.

Approach: Read count data, compute beta values, apply coverage filters, run Welch's t-test per CpG, correct for multiple testing with BH FDR, compute delta_beta, and write results.

import numpy as np
import pandas as pd
from scipy.stats import ttest_ind
from statsmodels.stats.multitest import multipletests

# Read count data: columns are cpg_id, {sample}_meth, {sample}_total
counts = pd.read_csv('bisulfite_counts.tsv', sep='\t', index_col='cpg_id')

# Identify samples and groups from column naming pattern
case_samples = [c.replace('_meth', '') for c in counts.columns if c.startswith('case') and c.endswith('_meth')]
ctrl_samples = [c.replace('_meth', '') for c in counts.columns if c.startswith('ctrl') and c.endswith('_meth')]

# Compute beta values: meth / total per CpG per sample
case_betas = pd.DataFrame({s: counts[f'{s}_meth'] / counts[f'{s}_total'] for s in case_samples}, index=counts.index)
ctrl_betas = pd.DataFrame({s: counts[f'{s}_meth'] / counts[f'{s}_total'] for s in ctrl_samples}, index=counts.index)

# Coverage filter: require minimum 10x in ALL samples
MIN_COVERAGE = 10  # 11 possible methylation levels, adequate power for testing
total_cols = [c for c in counts.columns if c.endswith('_total')]
passes_coverage = (counts[total_cols] >= MIN_COVERAGE).all(axis=1)
case_betas = case_betas[passes_coverage]
ctrl_betas = ctrl_betas[passes_coverage]

# Per-CpG Welch's t-test (vectorized)
t_stats, pvalues = ttest_ind(case_betas.values, ctrl_betas.values,
                              axis=1, equal_var=False, nan_policy='omit')

# BH FDR correction (default is Holm-Sidak, must specify fdr_bh)
reject, padj, _, _ = multipletests(pvalues, alpha=0.05, method='fdr_bh')

# Effect sizes
mean_case = case_betas.mean(axis=1)
mean_ctrl = ctrl_betas.mean(axis=1)
delta_beta = mean_case - mean_ctrl

# Assemble results
results = pd.DataFrame({
    'cpg_id': case_betas.index,
    'mean_case_beta': mean_case.values,
    'mean_ctrl_beta': mean_ctrl.values,
    'delta_beta': delta_beta.values,
    'pvalue': pvalues,
    'padj': padj,
    'significant': np.where(padj < 0.05, 'TRUE', 'FALSE')
})
results.to_csv('dmc.tsv', sep='\t', index=False)

Common Pitfalls

• Beta-value heteroscedasticity: Variance of beta values depends on methylation level -- highest near 0.5, compressed near 0 and 1. This means a 10% difference near beta=0 has different statistical properties than 10% near beta=0.5. For small samples, use limma on M-values instead.

• scipy.stats.ttest_ind defaults to Student's t-test (equal_var=True). Always pass equal_var=False for Welch's t-test. Equal variance between groups is almost never true for methylation data.

• statsmodels multipletests defaults to Holm-Sidak (method='hs'), not Benjamini-Hochberg. Always pass method='fdr_bh' explicitly.

• Fisher's exact test with replicates inflates false positives. Pooling methylated/unmethylated counts across biological replicates and running Fisher's test ignores biological variation, producing false positive rates of ~33%. Fisher's exact is only appropriate for unreplicated designs (single sample per group).

• methylKit meth.diff is not mean(case_beta) - mean(ctrl_beta). methylKit uses logistic regression with overdispersion correction. Its meth.diff column reflects the model-estimated difference, which can diverge from the simple mean difference, particularly at extreme methylation levels.

• Bonferroni correction is too conservative for genome-wide methylation. With 450K-850K CpGs (arrays) or 28M+ CpGs (WGBS), Bonferroni thresholds leave almost no significant CpGs. BH FDR is the standard approach.

• Cell-type composition confounds mixed-tissue samples. In blood or bulk tissue, observed methylation differences may reflect cell-type proportion changes rather than within-cell methylation changes (Jaffe & Irizarry 2014). Include cell-type estimates as covariates or use deconvolution methods.

Related Skills

• methylkit-analysis - Chi-squared testing with methylKit in R
• methylation-calling - Generate per-CpG count data from Bismark BAM files
• dmr-detection - Region-level testing after per-CpG analysis
• differential-expression/deseq2-basics - Analogous empirical Bayes concepts for count data
• proteomics/differential-abundance - Similar Welch t-test + BH workflow for proteomics