For estimating mean rates of change, we censored visual acuities of 20/20, except those that followed a lower value, to minimize a ceiling effect, because on our coding sheet we had constrained Snellen visual acuities to be ≤20/20. To minimize floor effects, we also censored patients with baseline visual acuities <20/100 and follow-up data after visual acuity declined to <20/100. For patients who became aphakic or pseudophakic in either eye at follow-up, those follow-up visits were excluded from visual acuity analyses. We also censored baseline visual field areas <78 deg
2 (i.e., equivalent to a diameter of 10°) and follow-up data after the first occurrence of an area <78 deg
2 to minimize floor effects. To minimize floor effects, we censored baseline ERG amplitudes <0.68 μV and follow-up data after the amplitude decreased to <0.34 μV. The censoring criteria were those applied in a previous study of patients with dominant
RHO mutations.
2 After applying these criteria, we eliminated patients from a given analysis if their residual follow-up was <3 years.
We converted all measures of ocular function to natural logarithms, because an exponential model has been shown to be optimal for evaluating cell loss over time in animal models of retinitis pigmentosa,
12 provides a good fit for describing short-term disease progression in patients with retinitis pigmentosa,
2 and has been used in several longitudinal studies of retinitis pigmentosa.
1 2 8 9 10 13 14 Repeated-measures longitudinal regression (performed with PROC MIXED of SAS, ver. 9; SAS Institute, Cary, NC) was used to estimate the mean rate of change for each outcome measure, based on the average log
e value for both eyes at each visit (when data for both eyes were available). By including terms for genotype (i.e.,
RPGR versus
RHO mutation) and the cross-product of time × genotype, we compared mean slopes in patients with
RPGR mutations versus mean slopes in patients with
RHO mutations. We also used longitudinal regression to compare the mean rates of progression in patients with
RPGR mutations in exons 1 to 14 (
n = 33) with the mean rates in patients who had
RPGR mutations in open reading frame (ORF) 15 (
n = 80), because a previous analysis had suggested differences in ocular function between these two groups based on single visits.
5
We used the commercial software (PROC LIFEREG of SAS) to fit a Weibull function to survival data and compare the age distribution of legal blindness in patients with RPGR mutations to the corresponding distribution in patients with RHO mutations. These plots provide a visualization of the long-term course of disease, and the model allows inclusion of left-censored data (i.e., a patient failing at baseline) and right-censored data (i.e., a patient not failing during follow-up) as well as interval-censored data (i.e., a patient failing between exams occurring at ages x1 and x2). For this purpose, we applied failure criteria (i.e., a visual acuity ≤20/200 or a visual field area ≤314 deg2 in one eye and a visual acuity ≤20/200 or a visual field area ≤314 deg2 in the fellow eye) to the entire dataset. The area of 314 deg2 corresponds to an equivalent diameter of 20° (i.e., a criterion for legal blindness) and was used in lieu of measuring the linear extent of each remaining visual field directly from charts. We also used a visual acuity ≤20/200 alone and a visual field area ≤314 deg2 alone as failure criteria, to determine which was the critical factor that led to legal blindness in each group.