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Sensitivity analysis for self-censoring: tilting, break-even values and calibration

Hsiu-Ting Yu

Why estimation alone cannot repair self-censoring

Under self-censoring (motif M2) the current state itself causes the skip: X_t -> R_t. No conditioning set of observed variables blocks this edge, so no estimator that uses only the answered prompts is consistent for the transition kernel (vignette("dm-graphs")), and the tests of vignette("testing-informativeness") can only say that silence was informative, not by how much. The remedy is a sensitivity analysis: fix the strength of self-censoring at a value delta, estimate as if that value were true, and repeat over a range of values. The result is not one estimate but a profile, together with the range of values (the identified set) that the data cannot rule out.

The package implements this as tilting. The selection model is a probit,

\[P(R_t = 1 \mid X_t = x) = \Phi_N(\alpha + \delta' x),\]

with the sensitivity vector delta held fixed (never estimated) and the intercept alpha calibrated so that the model-implied response rate given the observed history equals the observed response rate. Complete adjacent pairs are then reweighted by

\[w_t = \frac{P(R_t = 1 \mid x_{t-1})}{P(R_t = 1 \mid x_t)},\]

an inverse-probability weight with a stabilized numerator, and the within-person VAR(1) is refitted with these weights. Because the weights depend on the parameters and the parameters on the weights, the two steps are iterated to a fixed point. When delta is the true selection vector, the population parameters are a fixed point.

The running example

Eighty persons, forty prompts in eight days of five, 70% compliance, self-censoring on negative affect with delta = -1 (the propensity to respond drops by one probit unit per unit of negative affect), a passive sensor correlated .6 with the within-person fluctuations of negative affect, and 10% randomized probes that force a response.

sim <- simulate_ema(N = 80, n_prompts = 40, motifs = "M2", compliance = 0.7, delta = -1,
                    sensor_cor = 0.6, p_probe = 0.10, days = 5, seed = 21)
sim
#> Simulated EMA data: 80 persons x 40 prompts, 4 variables
#>   motifs: M2   realized response rate: 0.7
truth <- default_params()$Phi

One tilt: fit_tilt()

fit_tilt() fits the tilted VAR(1) at one sensitivity value. At delta = 0 it is the ordinary answered-pairs estimator of fit_pairs().

f0 <- fit_tilt(sim$data, sim$vars, delta = 0, day = "day", probe = "Z")
f1 <- fit_tilt(sim$data, sim$vars, delta = -1, day = "day", probe = "Z")
rbind(untilted = f0$Phi[1, ], tilted = f1$Phi[1, ], truth = truth[1, ])
#>               NegA         PosA    Stress     Fatigue
#> untilted 0.3528018 -0.004147836 0.1127210 0.026364308
#> tilted   0.4165011 -0.015654289 0.1328041 0.004728538
#> truth    0.4000000  0.000000000 0.1500000 0.000000000

Treating the skips as ignorable attenuates the autoregression of the self-censored variable (skipping the high moments cuts off the upper part of the trajectories); tilting at the true value moves the estimate toward the population value. The same holds for the means of the variables that the tilt touches (negative affect and, through their associations with it, positive affect and stress):

rbind(untilted = f0$mu, tilted = f1$mu, truth = default_params()$mu)
#>              NegA     PosA   Stress  Fatigue
#> untilted 1.980313 4.134264 2.566188 3.001217
#> tilted   2.297520 4.054181 2.755444 3.047208
#> truth    2.500000 4.000000 2.800000 3.000000

Two diagnostics accompany every tilt. The effective number of pairs, ess (the Kish measure \((\sum w)^2 / \sum w^2\)), says how much of the sample the weights still use, and max_weight flags a profile that rests on a few heavily weighted pairs. The weights are not truncated on purpose: a profile whose ess collapses is telling the analyst that the sensitivity value is extreme for these data.

c(pairs = f1$n_pairs, ess = round(f1$ess), max_weight = round(f1$max_weight, 2),
  iterations = f1$iterations, converged = f1$converged)
#>      pairs        ess max_weight iterations  converged 
#>     1379.0     1239.0        6.5       19.0        1.0

When a person propensity is declared with self-censoring (M2 + M4), propensity = "person" calibrates one intercept per person, so that stable between-person differences in compliance are not read as self-censoring.

The profile: tilt_profile()

tilt_profile() repeats the tilt over a grid, warm-starting each fit from its neighbor, and collects the lagged coefficients with cluster-robust confidence limits, the contemporaneous partial correlations and the between-person means.

prof <- tilt_profile(sim$data, sim$vars, delta_grid = seq(-2, 0.5, by = 0.5), day = "day", probe = "Z")
prof
#> Tilt profile over delta in { -2, -1.5, -1, -0.5, 0, 0.5 } for NegA 
#> Autoregressive coefficient of the self-censoring variable along the grid ( 1379 complete pairs):
#>  delta estimate lower upper  ess converged
#>   -2.0    0.483 0.378 0.588  540      TRUE
#>   -1.5    0.465 0.366 0.563  963      TRUE
#>   -1.0    0.417 0.344 0.489 1239      TRUE
#>   -0.5    0.369 0.312 0.426 1351      TRUE
#>    0.0    0.353 0.298 0.408 1379      TRUE
#>    0.5    0.393 0.332 0.454 1327      TRUE

The printed summary follows the autoregressive coefficient of the self-censoring variable along the grid. All coefficients are in prof$Phi, the partial correlations in prof$pcor and the means in prof$mu:

subset(prof$Phi, coef == "Stress<-NegA")[, c("delta", "estimate", "lower", "upper")]
#>    delta  estimate      lower     upper
#> 9   -2.0 0.2052495 0.11713650 0.2933625
#> 25  -1.5 0.1751215 0.10363392 0.2466092
#> 41  -1.0 0.1597695 0.09395294 0.2255860
#> 57  -0.5 0.1501252 0.08393873 0.2163117
#> 73   0.0 0.1479884 0.08020549 0.2157713
#> 89   0.5 0.1577502 0.08851590 0.2269845
subset(prof$pcor, edge == "NegA--Stress")
#>    delta         edge  estimate
#> 2   -2.0 NegA--Stress 0.2897371
#> 8   -1.5 NegA--Stress 0.2834852
#> 14  -1.0 NegA--Stress 0.2770801
#> 20  -0.5 NegA--Stress 0.2713879
#> 26   0.0 NegA--Stress 0.2662794
#> 32   0.5 NegA--Stress 0.2712504
round(prof$mu, 2)
#>      NegA PosA Stress Fatigue
#> [1,] 2.65 3.93   2.98    3.14
#> [2,] 2.47 3.99   2.86    3.09
#> [3,] 2.30 4.05   2.76    3.05
#> [4,] 2.14 4.10   2.66    3.02
#> [5,] 1.98 4.13   2.57    3.00
#> [6,] 1.78 4.20   2.45    2.99

The plot method draws selected coefficients against the sensitivity value. A plausible interval is shaded and a calibrated value can be marked:

plot(prof, plausible = c(-1.5, -0.5), calibrated = -1,
     main = "Effects of NegA at t - 1 along the sensitivity grid")

The sign convention: negative delta means that high states are skipped. Which sign applies is an empirical question that the silence test answers (vignette("testing-informativeness")): a negative coefficient of R_t there means the hidden states were higher, hence negative delta here.

Break-even values and identified sets: break_even()

For every lagged coefficient, break_even() reports the estimate at delta = 0, whether its interval excludes zero there, the smallest |delta| on the grid at which its sign or its significance status changes, and two ranges over the plausible interval |delta| <= delta_max: the identified set (the range of the point estimate) and the band (the range of the confidence limits).

be <- break_even(prof, delta_max = 1.5)
be[be$coef %in% c("NegA<-NegA", "Stress<-NegA", "PosA<-NegA"), ]
#>            coef  estimate_0 significant_0 sign_flip_delta
#> 6    NegA<-NegA  0.35280184          TRUE              NA
#> 10   PosA<-NegA -0.05239417         FALSE              NA
#> 14 Stress<-NegA  0.14798842          TRUE              NA
#>    significance_flip_delta  set_lower   set_upper  band_lower band_upper
#> 6                       NA  0.3528018  0.46466355  0.29759994 0.56284520
#> 10                     0.5 -0.1169179 -0.05239417 -0.22371627 0.01033641
#> 14                      NA  0.1479884  0.17512155  0.08020549 0.24660917

A coefficient whose identified set stays on one side of zero over the plausible interval is robust to self-censoring of that strength; one whose sign flips inside the interval is not. The significance-flip column is included because readers ask for it, but it is a dichotomous criterion and the band is the more informative summary.

The identified sets are narrow because the tilt uses the dynamics: what a person would have reported at a skipped prompt is constrained by the neighboring answered prompts. The worst-case bounds of bounds_support(), which allow every skipped value to lie anywhere on the response scale, ignore that information and are much wider. The comparison below is for the mean of negative affect: the range of the between-person mean over the plausible interval against the widths of the per-person support bounds on a 1 to 7 scale (the simulated states are unbounded, so the scale is nominal here).

range(prof$mu[abs(prof$delta_grid + 1) <= 0.5, "NegA"])          # identified set of the mean over [-1.5, -0.5]
#> [1] 2.138565 2.474371
b <- bounds_support(sim$data, sim$vars, L = 1, U = 7)
summary(b$upper[b$variable == "NegA"] - b$lower[b$variable == "NegA"])   # per-person support-bound widths
#>    Min. 1st Qu.  Median    Mean 3rd Qu.    Max. 
#>   0.000   1.050   1.650   1.802   2.438   4.350

Calibrating the sensitivity value: calibrate_delta()

A profile answers “what if”; a calibration answers “how much”. Three design features carry information about delta, and each maps an observed statistic onto the profile: the value of delta at which the fitted model reproduces the statistic is the calibrated value, and inverting the statistic’s confidence limits through the same curve gives an interval. All three are parametric calibrations, not identification results: they rely on the probit selection model and the VAR(1).

From a passive sensor

If an always-observed channel loads on the self-censored state, the sensor gap (sensor_gap_test()) is the amount by which the sensor differs at skipped prompts. The fitted tilt model implies a gap at every grid value; the calibrated delta is where the implied gap equals the observed one.

cs <- calibrate_delta(prof, sim$data, method = "sensor", day = "day")
cs
#> Calibration of delta (NegA) by the sensor method
#>   observed statistic: -0.455 (SE 0.055)
#>   calibrated delta: -0.841   95% interval: [-1.094, -0.618]
plot(cs, main = "Sensor calibration")

The curve is the model-implied sensor gap along the grid; the solid line is the observed gap with its confidence limits dashed, and the dotted vertical line is the calibrated value. cs$curve holds the numbers.

From randomized probes

Probe prompts are answered by design, so the states reported at probes are a random sample of the states, while ordinary answered prompts are a self-censored sample. The within-person contrast between the two is the probe contrast, and the fitted model implies its value at every grid point.

cp <- calibrate_delta(prof, sim$data, method = "probe", day = "day")
cp
#> Calibration of delta (NegA) by the probe method
#>   observed statistic: 0.222 (SE 0.069)
#>   calibrated delta: -1.004   95% interval: [-Inf, -0.353]

With 10% probes the contrast is estimated with less precision than the sensor gap, and one end of the interval is open (-Inf): one confidence limit of the observed contrast (here the upper one, because the probe contrast grows with the strength of self-censoring) lies beyond the largest value the model implies anywhere on the grid. An open end is reported as such rather than clipped; widening the grid would close it if the curve keeps rising.

From the post-skip contrast

Without a sensor or probes, the post-skip contrast of the silence test itself can be calibrated: data are simulated from the fitted tilt model at every grid value (n_sim data sets each), the silence test is run on them, and the model-implied contrast is compared with the observed one. This calibration needs no extra channel but relies entirely on the functional form.

ck <- calibrate_delta(prof, sim$data, method = "postskip", day = "day", n_sim = 5, seed = 2)
ck
#> Calibration of delta (NegA) by the postskip method
#>   observed statistic: -0.442 (SE 0.085)
#>   calibrated delta: -1.982   95% interval: [-Inf, -0.848]

The number of simulated data sets is kept small here; n_sim = 20 (the default) is appropriate in practice, and the Monte Carlo error of the curve is roughly the standard error of the post-skip coefficient divided by the square root of n_sim. In this example the calibrated value lies near the edge of the grid and the interval is open on one side: the post-skip contrast is a weak instrument at this sample size, which is what the simulation studies of Yu (2026) found as well.

data.frame(method = c("sensor", "probe", "postskip"),
           delta_hat = c(cs$delta_hat, cp$delta_hat, ck$delta_hat),
           lower = c(cs$interval[1], cp$interval[1], ck$interval[1]),
           upper = c(cs$interval[2], cp$interval[2], ck$interval[2]))
#>     method  delta_hat    lower      upper
#> 1   sensor -0.8409604 -1.09381 -0.6180643
#> 2    probe -1.0035532     -Inf -0.3532352
#> 3 postskip -1.9815965     -Inf -0.8478301

All three intervals contain the generating value of -1. The sensor calibration is the most precise; the probe (10% probes) and post-skip calibrations are much less precise, and both are open on one side here. In the simulation studies of Yu (2026) the post-skip calibration is less variable than the probe calibration but biased toward stronger self-censoring, whereas the sensor and probe calibrations are unbiased. When several calibrations are available, report them all with their sources and let the plausible interval for the sensitivity analysis cover their union rather than the tightest one.

Burden together with self-censoring

When burden (M3) is declared with self-censoring, the post-skip contrast also carries the collider contribution of R_t -> R_{t+1} <- X_{t+1}, which works against the self-censoring signal; an M2-only curve then understates |delta|. burden = "fit" simulates from a model with a burden term whose size is calibrated, at every grid value, so that the simulated response persistence (the response rate after an answered minus after a skipped prompt, fatigue_check()) matches the observed one.

sim23 <- simulate_ema(N = 60, n_prompts = 40, motifs = c("M2", "M3"), compliance = 0.7, delta = -1,
                      kappa_R = 1, days = 5, seed = 12)
prof23 <- tilt_profile(sim23$data, sim23$vars, delta_grid = c(-2, -1.5, -1, -0.5, 0), day = "day")
c_none <- calibrate_delta(prof23, sim23$data, method = "postskip", day = "day",
                          n_sim = 4, seed = 2, burden = "none")
c_fit <- calibrate_delta(prof23, sim23$data, method = "postskip", day = "day",
                         n_sim = 4, seed = 2, burden = "fit", kappa_grid = c(0, 0.5, 1, 1.5, 2))
c(M2_only = c_none$delta_hat, burden_fitted = c_fit$delta_hat)
#>       M2_only burden_fitted 
#>    -0.4610753    -1.1865462
c_fit$curve
#>   delta   predicted kappa_hat                              note
#> 1  -2.0 -0.50100415 0.0000000 persistence below simulated range
#> 2  -1.5 -0.46669925 0.1482803                                  
#> 3  -1.0 -0.03014104 1.0076219                                  
#> 4  -0.5  0.04830435 1.2057945                                  
#> 5   0.0  0.11950744 1.3368595

The kappa_hat column is the burden value matched at each grid point; a note marks grid points at which the observed persistence lay outside the simulated range.

Bootstrap intervals

The intervals above invert the confidence limits of the observed statistic through the fitted curve and ignore the sampling variability of the curve itself. boot > 0 adds a cluster bootstrap that resamples persons (or days, for single-person data), refits the profile on a coarse grid around the point estimate and recalibrates; the percentile interval of the replicates is reported alongside. It multiplies the running time by roughly the number of resamples, so it is not run in this vignette:

calibrate_delta(prof, sim$data, method = "sensor", day = "day", boot = 200, seed = 3)

Reporting: missingness_declaration()

The declaration collects the declared graph, the recoverability verdicts, the tests, the profile and the calibrations into a Markdown document for a preregistration or a paper. Sections whose objects are supplied are filled; the others remain as prompts.

g <- dm_graph("M2", sensor = TRUE, probe = TRUE)
st <- silence_test(sim$data, sim$vars, day = "day")
sg <- sensor_gap_test(sim$data, sim$vars, sensor = "S", day = "day")
decl <- missingness_declaration(g, silence = st, sensor_gap = sg, profile = prof,
                                calibration = list(cs, cp, ck), plausible = c(-1.5, -0.5))
cat(decl[grep("^## 5", decl):length(decl)], sep = "\n")
#> ## 5. Sensitivity analysis
#> - Sensitivity parameter: delta, probit units per unit of NegA; grid {-2, -1.5, -1, -0.5, 0, 0.5}; response-model intercept: common
#> - Effective number of complete pairs along the grid: 540, 963, 1239, 1351, 1379, 1327 (of 1379)
#> - Calibration by the sensor method: delta = -0.841, 95% interval [-1.094, -0.618]
#> - Calibration by the probe method: delta = -1.004, 95% interval [-Inf, -0.353]
#> - Calibration by the postskip method: delta = -1.982, 95% interval [-Inf, -0.848]
#> - Plausible interval used for the band: [-1.500, -0.500]
#> - Identified set and band over the plausible interval (effects of the self-censoring variable):
#>     - Fatigue<-NegA: estimate at delta = 0: 0.010; set [0.006, 0.042]; band [-0.071, 0.144]; sign change at none on the grid; significance change at none on the grid
#>     - NegA<-NegA: estimate at delta = 0: 0.353; set [0.353, 0.465]; band [0.298, 0.563]; sign change at none on the grid; significance change at none on the grid
#>     - PosA<-NegA: estimate at delta = 0: -0.052; set [-0.117, -0.052]; band [-0.224, 0.010]; sign change at none on the grid; significance change at 0.500
#>     - Stress<-NegA: estimate at delta = 0: 0.148; set [0.148, 0.175]; band [0.080, 0.247]; sign change at none on the grid; significance change at none on the grid
#> 
#> ## 6. What is reported in the paper
#> - Estimates under the declared graph, the sensitivity band, and this declaration.

Practical recommendations

References

Kish, L. (1965). Survey sampling. Wiley.

Yu, H.-T. (2026). What skipped prompts hide: Detecting, diagnosing, and correcting informative nonresponse in ecological momentary assessment. Manuscript under review.

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