# Dynamic Failure Rate Distributions

## Introduction

The `flexhaz` package provides a flexible framework for working with survival distributions defined through their hazard (failure rate) functions. Instead of choosing from a fixed catalog of distributions, you directly specify the hazard function itself, giving complete flexibility to model systems with complex, time-varying failure patterns.

### Why hazard-based parameterization?

Traditional approaches use parametric families (Weibull, exponential, log-normal) that impose strong assumptions on failure rate behavior. The hazard function \(h(t)\) provides a more intuitive parameterization for reliability:

- Constant hazard: Exponential distribution (memoryless failures)
- Increasing hazard: Wear-out phenomena
- Decreasing hazard: Burn-in or infant mortality
- Bathtub curve: Common in electronics and human mortality

### Mathematical background

For a lifetime random variable \(T\), the instantaneous failure rate (hazard) is: \[ h(t) = \lim_{\Delta t \to 0} \frac{\Pr\{T \leq t + \Delta t | T > t\}}{\Delta t} = \frac{f(t)}{S(t)} \]

The cumulative hazard integrates the instantaneous rate: \[ H(t) = \int_0^t h(u) \, du \]

From this, all other quantities follow:

- Survival function: \(S(t) = \exp(-H(t))\)
- CDF: \(F(t) = 1 - S(t)\)
- PDF: \(f(t) = h(t) \cdot S(t)\)

## Getting Started

    library(flexhaz)

### Using Built-in Distributions

The package provides convenient constructors for classic survival distributions:

    # Exponential: constant hazard h(t) = lambda
    exp_dist <- dfr_exponential(lambda = 0.5)

    # Weibull: power-law hazard h(t) = (k/sigma)(t/sigma)^(k-1)
    weib_dist <- dfr_weibull(shape = 2, scale = 3)

    # Gompertz: exponentially increasing hazard h(t) = a*exp(b*t)
    gomp_dist <- dfr_gompertz(a = 0.01, b = 0.1)

    # Log-logistic: non-monotonic hazard (increases then decreases)
    ll_dist <- dfr_loglogistic(alpha = 10, beta = 2)

    print(exp_dist)
    #> Dynamic failure rate (DFR) distribution with failure rate:
    #> function (t, par, ...)
    #> {
    #>     rep(par[[1]], length(t))
    #> }
    #> <bytecode: 0x6425c246fd78>
    #> <environment: 0x6425c0541dc0>
    #> It has a survival function given by:
    #>     S(t|rate) = exp(-H(t,...))
    #> where H(t,...) is the cumulative hazard function.
    is_dfr_dist(exp_dist)
    #> [1] TRUE

### Creating Custom Distributions

For non-standard hazard patterns, use `dfr_dist()` directly:

    # Custom: linear increasing hazard h(t) = a + b*t
    linear_dist <- dfr_dist(
      rate = function(t, par, ...) {
        a <- par[1]
        b <- par[2]
        a + b * t
      },
      par = c(a = 0.1, b = 0.01)
    )

The `rate` function must accept:

- `t`: time (scalar or vector)
- `par`: parameter vector
- `...`: additional arguments

See `vignette("custom_distributions")` for detailed guidance on creating optimized custom distributions.

## Distribution Methods

All standard distribution functions are available:

### Hazard and cumulative hazard

    h <- hazard(exp_dist)
    H <- cum_haz(exp_dist)

    # Evaluate at specific times
    h(1)      # Hazard at t=1
    #> [1] 0.5
    h(c(1, 2, 3))  # Vectorized
    #> [1] 0.5 0.5 0.5

    H(2)      # Cumulative hazard at t=2
    #> [1] 1

### Survival and CDF

    S <- surv(exp_dist)
    F <- cdf(exp_dist)

    # Verify S(t) + F(t) = 1
    t <- 2
    c(survival = S(t), cdf = F(t), sum = S(t) + F(t))
    #>  survival       cdf       sum
    #> 0.3678794 0.6321206 1.0000000

### PDF (Density)

    # Use stats::density which flexhaz implements as density.dfr_dist
    pdf_fn <- density(exp_dist)

    # For exponential: f(t) = lambda * exp(-lambda * t)
    t <- 1
    lambda <- 0.5
    c(computed = pdf_fn(t), analytical = lambda * exp(-lambda * t))
    #>   computed analytical
    #>  0.3032653  0.3032653

### Quantile function (inverse CDF)

    Q <- inv_cdf(exp_dist)

    # Median of exponential is log(2)/lambda
    median_computed <- Q(0.5)
    median_analytical <- log(2) / 0.5
    c(computed = median_computed, analytical = median_analytical)
    #>   computed analytical
    #>   1.386294   1.386294

### Sampling

    samp <- sampler(exp_dist)

    set.seed(42)
    samples <- samp(1000)

    # Compare sample mean to theoretical mean (1/lambda = 2)
    c(sample_mean = mean(samples), theoretical = 1/0.5)
    #> sample_mean theoretical
    #>     1.92733     2.00000

### Overriding parameters

All methods accept a `par` argument to override default parameters:

    h <- hazard(exp_dist)

    # Use default lambda = 0.5
    h(1)
    #> [1] 0.5

    # Override with lambda = 2
    h(1, par = c(2))
    #> [1] 2

## Likelihood Model Interface

The `dfr_dist` class implements the likelihood.model interface, enabling maximum likelihood estimation with survival data.

### Log-likelihood for survival data

For exact observations (failures at known times): \[ \log L_i = \log h(t_i) - H(t_i) \]

For right-censored observations (survived past time \(t\)): \[ \log L_i = -H(t_i) \]

### Creating test data

    # Simulate exact failure times from exponential(lambda=1)
    set.seed(123)
    true_lambda <- 1
    n <- 50
    times <- rexp(n, rate = true_lambda)

    # Create data frame with standard survival format
    # delta = 1 means exact observation, delta = 0 means censored
    df_exact <- data.frame(t = times, delta = rep(1, n))
    head(df_exact)
    #>            t delta
    #> 1 0.84345726     1
    #> 2 0.57661027     1
    #> 3 1.32905487     1
    #> 4 0.03157736     1
    #> 5 0.05621098     1
    #> 6 0.31650122     1

### Computing log-likelihood

    dist <- dfr_dist(
      rate = function(t, par, ...) rep(par[1], length(t)),
      par = NULL  # No default - must be supplied
    )

    ll <- loglik(dist)

    # Evaluate at different parameter values
    ll(df_exact, par = c(0.5))  # lambda = 0.5
    #> [1] -62.91663
    ll(df_exact, par = c(1.0))  # lambda = 1.0 (true value)
    #> [1] -56.51854
    ll(df_exact, par = c(2.0))  # lambda = 2.0
    #> [1] -78.37973

The log-likelihood should be highest near the true parameter value.

### Score function (gradient)

The score function is the gradient of the log-likelihood with respect to parameters. It’s computed numerically by default:

    s <- score(dist)
    s(df_exact, par = c(1.0))  # Should be close to 0 at MLE
    #> [1] -6.518543

### Hessian of log-likelihood

    H_ll <- hess_loglik(dist)
    hess <- H_ll(df_exact, par = c(1.0))
    hess  # Should be negative (concave at maximum)
    #>      [,1]
    #> [1,]  -50

## Maximum Likelihood Estimation

The `fit()` function provides MLE estimation:

    solver <- fit(dist)

    # Find MLE starting from initial guess
    result <- solver(df_exact, par = c(0.5), method = "BFGS")

    # Extract fitted parameters (the fisher_mle class from likelihood.model uses coef())
    coef(result)
    #> [1] 0.8846654

    # Compare to analytical MLE: lambda_hat = n / sum(t)
    analytical_mle <- n / sum(times)
    c(fitted = coef(result), analytical = analytical_mle, true = true_lambda)
    #>     fitted analytical       true
    #>  0.8846654  0.8846654  1.0000000

### Working with censored data

Real survival data often includes censoring. Here’s an example with mixed data:

    # Some observations are censored (patient still alive at study end)
    df_mixed <- data.frame(
      t = c(1, 2, 3, 4, 5, 6, 7, 8),
      delta = c(1, 1, 1, 0, 0, 1, 1, 0)  # 0 = censored
    )

    ll <- loglik(dist)

    # Fit with censored data
    solver <- fit(dist)
    result <- solver(df_mixed, par = c(0.5), method = "BFGS")
    coef(result)
    #> [1] 0.1388889

## Example: Weibull MLE

    # Create Weibull DFR
    weibull <- dfr_dist(
      rate = function(t, par, ...) {
        k <- par[1]
        sigma <- par[2]
        (k / sigma) * (t / sigma)^(k - 1)
      }
    )

    # Simulate Weibull data (shape=2, scale=3)
    set.seed(456)
    true_shape <- 2
    true_scale <- 3
    n <- 100

    # Use inverse CDF sampling
    u <- runif(n)
    weibull_times <- true_scale * (-log(u))^(1/true_shape)

    df_weibull <- data.frame(t = weibull_times, delta = rep(1, n))

    # Fit
    solver <- fit(weibull)
    result <- solver(df_weibull, par = c(1.5, 2.5), method = "BFGS")

    c(fitted_shape = coef(result)[1], true_shape = true_shape)
    #> fitted_shape   true_shape
    #>      1.92518      2.00000
    c(fitted_scale = coef(result)[2], true_scale = true_scale)
    #> fitted_scale   true_scale
    #>     2.788113     3.000000

## Custom Hazard Functions

The real power of `flexhaz` is modeling complex, non-standard hazard patterns.

### Bathtub hazard

A classic bathtub curve has three phases: 1. Infant mortality: High initial failure rate that decreases 2. Useful life: Low, relatively constant failure rate 3. Wear-out: Increasing failure rate as components age

    # h(t) = a * exp(-b*t) + c + d * t^k
    # Three components: infant mortality + baseline + wear-out
    bathtub <- dfr_dist(
      rate = function(t, par, ...) {
        a <- par[1]  # infant mortality magnitude
        b <- par[2]  # infant mortality decay rate
        c <- par[3]  # baseline hazard (useful life)
        d <- par[4]  # wear-out coefficient
        k <- par[5]  # wear-out exponent
        a * exp(-b * t) + c + d * t^k
      },
      par = c(a = 1, b = 2, c = 0.02, d = 0.001, k = 2)
    )

    # Plot the hazard function
    t_seq <- seq(0.01, 15, length.out = 200)
    h <- hazard(bathtub)
    plot(t_seq, sapply(t_seq, h), type = "l",
         xlab = "Time", ylab = "Hazard rate",
         main = "Bathtub hazard curve")

### Time-covariate interaction

Hazards can depend on covariates that modify the time effect:

    # Proportional hazards with covariate x
    # h(t, x) = h0(t) * exp(beta * x)
    # where h0(t) = Weibull baseline

    ph_model <- dfr_dist(
      rate = function(t, par, x = 0, ...) {
        k <- par[1]
        sigma <- par[2]
        beta <- par[3]
        baseline <- (k / sigma) * (t / sigma)^(k - 1)
        baseline * exp(beta * x)
      },
      par = c(shape = 2, scale = 3, beta = 0.5)
    )

    h <- hazard(ph_model)

    # Hazard for different covariate values
    h(2, x = 0)  # Baseline
    #>     shape
    #> 0.4444444
    h(2, x = 1)  # Higher risk group
    #>    shape
    #> 0.732765

## Integration with algebraic.dist

The `dfr_dist` class inherits from algebraic.dist classes, providing access to additional functionality:

    # Support is (0, Inf) for all DFR distributions
    support <- sup(exp_dist)
    print(support)
    #> (0, Inf)

    # Parameters
    params(exp_dist)
    #> [1] 0.5

## Model Diagnostics

After fitting a model, it’s essential to verify goodness-of-fit. The package provides diagnostic tools based on residual analysis.

### Cox-Snell Residuals

Cox-Snell residuals are defined as r_i = H(t_i), the cumulative hazard at each observation time. If the model is correctly specified, these residuals follow an Exp(1) distribution.

    # Fit a model and check residuals
    set.seed(99)
    test_times <- rexp(80, rate = 0.3)
    test_df <- data.frame(t = test_times, delta = 1)

    # Fit exponential
    exp_fitted <- dfr_exponential()
    solver <- fit(exp_fitted)
    fit_result <- solver(test_df, par = c(0.5))
    lambda_hat <- coef(fit_result)

    # Create fitted distribution with estimated parameters
    exp_final <- dfr_exponential(lambda = lambda_hat)

    # Q-Q plot of Cox-Snell residuals
    qqplot_residuals(exp_final, test_df)

Points falling along the diagonal indicate good fit. Systematic departures suggest model misspecification.

### Martingale Residuals

Martingale residuals (M_i = delta_i - H(t_i)) are useful for identifying individual observations that are poorly fit:

    mart_resid <- residuals(exp_final, test_df, type = "martingale")
    summary(mart_resid)
    #>    Min. 1st Qu.  Median    Mean 3rd Qu.    Max.
    #> -4.8856 -0.4127  0.3650  0.0000  0.7569  0.9998

    # Large positive values: failed earlier than expected
    # Large negative values: survived longer than expected

For more detailed diagnostic workflows, see `vignette("reliability_engineering")`.

## Summary

The `flexhaz` package provides:

1. Flexible specification: Define distributions through hazard functions
2. Complete distribution interface: hazard, survival, CDF, PDF, quantiles, sampling
3. Likelihood model support: Log-likelihood, score, Hessian for MLE
4. Censoring support: Handle exact, right-censored, and left-censored survival data
5. Numerical integration: Automatic computation of cumulative hazard
6. Model diagnostics: Residuals and Q-Q plots for fit assessment

This makes it ideal for:

- Custom reliability models
- Survival analysis with non-standard hazard patterns
- Maximum likelihood estimation of hazard function parameters
- Simulation studies with flexible failure distributions

## Next Steps

- `vignette("flexhaz-package")` - Package introduction and quick start
- `vignette("reliability_engineering")` - Five real-world case studies
- `vignette("custom_distributions")` - The three-level optimization paradigm
- `vignette("custom_derivatives")` - Supplying analytical score and Hessian functions