insurance-frequency-severity 0.2.7

Sarmanov copula joint frequency-severity modelling for UK personal lines insurance, with neural two-part dependent model

insurance-frequency-severity

Sarmanov copula joint frequency-severity modelling for UK personal lines insurance.

Merged from: insurance-frequency-severity (Sarmanov/Gaussian copula) and insurance-dependent-fs (neural two-part model).

Blog post: Your Frequency-Severity Independence Assumption Is Costing You Premium

Challenges the independence assumption in the standard two-model GLM framework. Your frequency GLM and severity GLM are correct. The problem is multiplying their predictions together as though claim count and average severity are unrelated — they are not.

The problem

Every UK motor pricing team runs two GLMs:

Pure premium = E[N|x] × E[S|x]

This assumes N and S are independent given rating factors x. The assumption is almost certainly wrong. In UK motor, the No Claims Discount structure suppresses borderline claims: policyholders with frequent small claims are aware of the NCD threshold and do not report near-miss incidents. The result is a systematic negative correlation between claim count and average severity.

Vernic, Bolancé, and Alemany (2022) found this mismeasurement amounts to €5–55+ per policyholder on a Spanish auto book. The directional effect in UK motor is the same; the magnitude depends on your book.

This library gives you three methods to measure and correct for it:

1. Sarmanov copula (primary): Bivariate Sarmanov distribution for NB/Poisson frequency × Gamma/Lognormal severity. Handles the discrete-continuous mixed margins problem correctly — no probability integral transform approximation needed for the count margin. IFM estimation: you plug in your fitted GLM objects, we estimate omega.

2. Gaussian copula (comparison): Standard approach from Czado et al. (2012). Uses PIT approximation for the discrete margin. Good for presenting rho in familiar terms.

3. Garrido conditional (fallback): Adds N as a covariate in the severity GLM. No copula, no new methodology — just a single extra GLM parameter. Works on smaller books where omega estimation would be unreliable.

Installation

uv add insurance-frequency-severity

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Quickstart

import numpy as np
import pandas as pd
import statsmodels.api as sm
from insurance_frequency_severity import JointFreqSev, DependenceTest

rng = np.random.default_rng(42)
n_policies = 5000
# Synthetic motor book: claim count and average severity per policy
claim_count = rng.poisson(0.10, size=n_policies)
avg_severity = np.where(
    claim_count > 0,
    rng.gamma(shape=3.0, scale=800.0, size=n_policies),
    np.nan,
)
X = np.column_stack([
    rng.normal(35, 8, n_policies),   # age
    rng.normal(5, 2, n_policies),    # ncb
])
claims_df = pd.DataFrame({
    "claim_count": claim_count,
    "avg_severity": avg_severity,
})

# Fit marginal GLMs
X_df = pd.DataFrame(X, columns=["age", "ncb"])
X_const = sm.add_constant(X_df)
my_nb_glm = sm.GLM(
    claim_count, X_const, family=sm.families.NegativeBinomial(alpha=0.8)
).fit()
claims_mask = claim_count > 0
my_gamma_glm = sm.GLM(
    avg_severity[claims_mask],
    X_const[claims_mask],
    family=sm.families.Gamma(link=sm.families.links.Log()),
).fit()

# Test for dependence first
test = DependenceTest()
test.fit(n=claim_count[claims_mask], s=avg_severity[claims_mask])
print(test.summary())

# Fit joint model — accepts your existing fitted GLMs
model = JointFreqSev(
    freq_glm=my_nb_glm,    # fitted statsmodels NegativeBinomial GLM
    sev_glm=my_gamma_glm,  # fitted statsmodels Gamma GLM
    copula="sarmanov",
)
model.fit(
    claims_df,
    n_col="claim_count",
    s_col="avg_severity",
)

# Check dependence parameter and confidence interval
print(model.dependence_summary())

# Get correction factors for your in-force book
corrections = model.premium_correction()
print(corrections[["mu_n", "mu_s", "correction_factor", "premium_joint"]].describe())

GLM compatibility

This library is designed for statsmodels GLM objects. It detects marginal families via model.family (statsmodels convention) and extracts dispersion from model.scale. Non-statsmodels objects with .predict() and .fittedvalues may work, but kernel parameters will be inferred from statsmodels-specific attributes and could silently produce wrong results. For non-statsmodels GLMs, pass parameter dictionaries directly.

# Works with statsmodels GLM results
import statsmodels.api as sm
import numpy as np
import pandas as pd

rng = np.random.default_rng(0)
n = 3000
X = pd.DataFrame({"age": rng.normal(35, 8, n), "ncb": rng.normal(5, 2, n)})
X_const = sm.add_constant(X)
y = rng.poisson(0.10, size=n)
claims_mask = y > 0
s = rng.gamma(3.0, 800.0, size=n)

nb_glm = sm.GLM(y, X_const, family=sm.families.NegativeBinomial(alpha=0.8)).fit()
gamma_glm = sm.GLM(
    s[claims_mask],
    X_const[claims_mask],
    family=sm.families.Gamma(link=sm.families.links.Log()),
).fit()

model = JointFreqSev(freq_glm=nb_glm, sev_glm=gamma_glm)

Methods

JointFreqSev

model = JointFreqSev(freq_glm, sev_glm, copula="sarmanov")
model.fit(data, n_col, s_col, method="ifm")   # IFM or MLE
model.premium_correction()                    # DataFrame with correction factors
model.loss_cost(X_new)                        # Corrected pure premium for new data
model.dependence_summary()                    # omega, CI, Spearman rho, AIC/BIC

# Note: for copula="gaussian" or "fgm", premium_correction() returns a single
# portfolio-average correction factor applied to all policies. Per-policy
# analytical corrections are available with copula="sarmanov" only.

ConditionalFreqSev (Garrido 2016)

from insurance_frequency_severity import ConditionalFreqSev

model = ConditionalFreqSev(freq_glm, sev_glm_base)
model.fit(data, n_col, s_col)
model.premium_correction()   # Correction = exp(gamma) * exp(mu_n * (exp(gamma) - 1))

Diagnostics

import numpy as np
import pandas as pd
import statsmodels.api as sm
from insurance_frequency_severity import DependenceTest, compare_copulas, JointFreqSev

rng = np.random.default_rng(0)
n_policies = 5000
n = rng.poisson(0.10, size=n_policies)
s = np.where(n > 0, rng.gamma(3.0, 800.0, size=n_policies), np.nan)
X = pd.DataFrame({"age": rng.normal(35, 8, n_policies)})
X_const = sm.add_constant(X)
freq_glm = sm.GLM(n, X_const, family=sm.families.Poisson()).fit()
claims_mask = n > 0
sev_glm = sm.GLM(
    s[claims_mask], X_const[claims_mask],
    family=sm.families.Gamma(link=sm.families.links.Log()),
).fit()
n_positive = n[claims_mask]
s_positive = s[claims_mask]

# Test independence
test = DependenceTest(n_permutations=1000)
test.fit(n_positive, s_positive)
print(test.summary())   # Kendall tau, Spearman rho, permutation p-values

# AIC/BIC comparison across copula families
comparison = compare_copulas(n, s, freq_glm, sev_glm)
print(comparison)   # Sorted by AIC: sarmanov, gaussian, fgm

Report

from insurance_frequency_severity import JointModelReport

report = JointModelReport(model, dependence_test=test, copula_comparison=comparison)
report.to_html(
    "pricing_review.html",
    n=n,
    s=s,
    correction_df=corrections,
)

Premium correction interpretation

The correction factor is E[N×S] / (E[N] × E[S]). Values:

• < 1.0: negative dependence. High-count policyholders have lower severity than independence predicts. Independence model overstates their risk.
• = 1.0: independence holds.
• > 1.0: positive dependence. Rare but valid — e.g., some commercial lines where large customers have both high frequency and high severity.

For UK motor with typical NCD structure, expect the average correction to be 0.93–0.98 (independence overstates the pure premium by 2–7% on average, with larger corrections at the high-frequency tail).

Theoretical background

The Sarmanov bivariate distribution:

f(n, s) = f_N(n) × f_S(s) × [1 + ω × φ₁(n) × φ₂(s)]

where φ₁, φ₂ are bounded kernel functions with zero mean under their respective marginals. When ω=0 this reduces to the product of marginals (independence). The key advantage over standard copulas: no probability integral transform is needed for the discrete frequency margin. Sklar's theorem is not unique for discrete distributions, so the "copula" of a discrete-continuous pair is not well-defined. The Sarmanov family sidesteps this entirely by working directly with the joint distribution.

Spearman's rho range for the Laplace kernel Sarmanov with NB/Gamma margins: [-3/4, 3/4] (Blier-Wong 2026). This comfortably accommodates the moderate negative dependence found in auto insurance data.

The IFM (Inference Functions for Margins) estimator:

1. Fit frequency GLM → get E[N|xᵢ] for each policy
2. Fit severity GLM → get E[S|xᵢ] for each claiming policy
3. Profile likelihood over ω: maximise Σᵢ log[1 + ω × φ₁(nᵢ; μ̂ᴺᵢ) × φ₂(sᵢ; μ̂ˢᵢ)] for observed (nᵢ, sᵢ) with nᵢ > 0

Zero-claim policies contribute no severity information; their likelihood contribution is just f_N(0), which does not depend on ω. So only observed claims inform the dependence estimate.

Data requirements

Stable ω estimation needs approximately 20,000 policyholder-years with at least 2,000 claims. Smaller portfolios will produce wide confidence intervals on ω. The library warns you at < 1,000 policies and < 500 claims.

For small books, use ConditionalFreqSev — it estimates a single parameter γ from the severity GLM refitted with N as a covariate, which is more stable with less data.

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Performance

Benchmarked against an independent two-part model (Poisson GLM × Gamma GLM, pure premium = E[N] × E[S]) on 12,000 synthetic UK motor policies (8,437 train / 3,563 test) with known positive freq-sev dependence via a latent risk score. Results from benchmarks/benchmark_insurance_frequency_severity.py run 2026-03-16.

Metric	Independent model	Sarmanov copula	Change
Pure premium MAE vs oracle	14.8405	10.6010	-28.6%
Portfolio total premium bias	+22.95%	-6.77%	-16.2pp
Estimated Spearman rho	0.000	-0.015	—
Fit time (seconds)	0.105	0.128	+21%

Correction factors: mean 0.943, p10 0.939, p90 0.950. High-risk decile correction: 0.952 (-4.8% premium reduction vs independence). Low-risk decile: 0.940.

Note on omega sign: The benchmark DGP uses a positive latent risk score (z) to drive both higher frequency and severity. The fitted omega is -1.14 (Spearman rho ≈ -0.015), meaning the library detected negative-leaning dependence on this sample. The 95% CI on omega is (-1.61, +0.30), which includes zero — independence is not rejected at 5%. Despite this, the correction produces a 28.6% MAE improvement and reduces portfolio bias from +22.95% to -6.77%. This is explained by the correction absorbing some of the marginal model error: the GLMs slightly overpredict frequency for high-latent-risk policies, and the copula correction partially offsets this.

The canonical use case is a portfolio where omega is positive and statistically significant. Use DependenceTest before fitting to check whether the correction is supported by the data.

When to use: Personal lines motor or property books where DependenceTest indicates positive and statistically significant freq-sev dependence. The correction is analytical (closed-form, no simulation at scoring time).

When NOT to use: When you cannot reject independence (DependenceTest p-value > 0.05). Also when the book has very few claims (< 500) — the omega estimate will be too noisy.

Databricks Notebook

A ready-to-run Databricks notebook benchmarking this library against standard approaches is available in burning-cost-examples.

References

• Vernic, Bolancé, Alemany (2022). Sarmanov distribution for modeling dependence between the frequency and the average severity of insurance claims. Insurance: Mathematics and Economics, 102, 111–125.
• Garrido, Genest, Schulz (2016). Generalized linear models for dependent frequency and severity of insurance claims. IME, 70, 205–215.
• Lee, Shi (2019). A dependent frequency-severity approach to modeling longitudinal insurance claims. IME, 87, 115–129.
• Blier-Wong (2026). arXiv:2601.09016. Spearman rho range for Sarmanov copulas.
• Czado, Kastenmeier, Brechmann, Min (2012). A mixed copula model for insurance claims and claim sizes. Scandinavian Actuarial Journal, 4, 278–305.

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Built by Burning Cost. MIT licence.

Related Libraries

Library	What it does
insurance-dispersion	Double GLM for covariate-driven dispersion — models heterogeneous variance within each component
insurance-severity	Heavy-tail severity with composite Pareto models and ILFs — use for the severity component when tails matter
insurance-quantile	Quantile GBM for tail risk — non-parametric complement when the full distributional structure is uncertain

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Part of the Burning Cost Toolkit

Open-source Python libraries for UK personal lines insurance pricing. Browse all libraries

Library	Description
insurance-conformal	Distribution-free prediction intervals — FrequencySeverityConformal provides joint f/s coverage guarantees
insurance-credibility	Bühlmann-Straub credibility — blends frequency and severity estimates for thin segments
insurance-causal	DML causal inference — establishes whether frequency-severity dependence is causal or driven by observed confounders
insurance-monitoring	Model drift detection — monitors frequency and severity component calibration separately over time
insurance-governance	Model validation and MRM governance — produces the sign-off pack for joint frequency-severity models