Phase I Study of the Safety, Tolerability, PK & PD of Lomitapide in Japanese and Caucasian Subjects With Elevated LDL-C: Complete Statistical Analysis

1. Trial at a Glance

This page covers the registry results for Phase I Study of the Safety, Tolerability, PK & PD of Lomitapide in Japanese and Caucasian Subjects With Elevated LDL-C (NCT01760187), a randomized phase 1 study. The primary outcome is Cmax for Lomitapide.

2. Clinical Question

The registry describes a randomized, double-blind, placebo-controlled phase I study. Its stated purpose was to evaluate pharmacokinetics and pharmacodynamics in Japanese participants as compared with Caucasian participants. The primary result focuses on plasma concentration rather than a health outcome or a treatment effect on elevated LDL-C. The posted arm summaries also describe the higher dose cohorts, allowing the concentration pattern across dose levels and populations to be considered descriptively. Those cohort summaries do not replace the primary 10 mg comparison or establish a formally tested population difference across doses.

3. Trial Design

This was a phase I randomized, double-blind, placebo-controlled, parallel study with quadruple masking, according to the registry record. It is described as a single ascending dose and multiple ascending dose study of orally administered lomitapide. The study status is completed. The recorded enrollment is 72. The listed dates are a start date of 2012-11-07 and a primary completion date of 2013-06-03.

The cohort descriptions divide participants by ancestry group and dose. Cohort 1 included Japanese and Caucasian participants assigned to 10 mg lomitapide or placebo; Cohort 2 used 20 mg, Cohort 3 used 40 mg, and Cohort 4 used 60 mg, each with placebo participants. The registry describes a randomized allocation, but further details of the randomization process are not reported in the registry record. The way the single-dose and multiple-dose parts relate operationally, including the exact dosing schedules, is not reported in the registry record.

The primary endpoint is Cmax for lomitapide, summarized as a mean and standard deviation. The endpoint population is stated as all subjects with evaluable concentrations. The posted primary arm summaries cover Japanese and Caucasian participants in each of the four lomitapide dose groups. The unadjusted comparison posted for interpretation is between the two 10 mg groups; a corresponding posted inferential comparison for the higher dose groups is not reported in the registry record.

The registry lists 27 outcome measures and no reported analyses. A detailed protocol, original statistical analysis plan, eligibility criteria beyond the healthy-volunteer description, and justification for the enrollment target are not reported in the registry record. The presence of randomization and masking describes study design, but does not by itself establish how every analysis was conducted or whether the posted groups are comparable on all relevant characteristics.

4. Participant Flow and Accounting

The registry reports how participants moved through each stage of the study. All counts below are exactly as posted; missing counts are not inferred from other stages.

Overall Study

Analysis population for the primary outcome, as defined in the registry: All subjects with evaluable concentrations

5. Baseline Characteristics

The table reproduces the baseline characteristics posted in the registry, which describe the participants analysed at baseline and help show whether the randomized groups were comparable.

Only the first 6 of 11 groups are shown.

6. Primary Endpoint

The registry lists the primary outcome as Cmax for Lomitapide, measured over 1, 2, 4, 6, 8, 12, 24, 48, 72, 96, 120, 144, and 168 hours postdose on Day 7.

The primary endpoint is the maximum observed plasma concentration of lomitapide, known as Cmax, measured in ng/mL. The registry describes it as the maximum observed plasma concentration and specifies that concentrations were assessed at 1, 2, 4, 6, 8, 12, 24, 48, 72, 96, 120, 144, and 168 hours postdose on Day 7. The reported endpoint is a continuous pharmacokinetic measure summarized by its mean and standard deviation in each group.

Cmax is used in pharmacokinetic studies to describe the highest measured concentration after dosing. It can characterize systemic drug exposure and support comparisons of concentration profiles between groups or dose cohorts. In this study, the stated scientific interest was to evaluate pharmacokinetics and pharmacodynamics in Japanese participants as compared with Caucasian participants. The primary endpoint therefore addresses a concentration-based question within the study’s stated purpose.

Cmax does not, on its own, describe the full concentration-time profile: it does not convey when the maximum occurred or how long concentrations remained elevated. Other listed outcomes, including Tmax and area under the curve measures, address different features of exposure. Nor is Cmax itself a measure of clinical benefit, harm, or a change in LDL-C. Its interpretation is limited to the pharmacokinetic outcome and the population and dose groups represented in the posted results.

7. Results Posted in the Registry

• Caucasian 10 mg: mean 0.44 versus 0.57 on control; difference -0.13 (95% CI -0.34 to 0.07), standardized effect d = -0.57; z-test p = 0.199.

8. Secondary Efficacy Endpoints

The registry also posts results for secondary outcomes. For each outcome below, the endpoint type, the test applied to the posted summary statistics, the result and its interpretation are given in turn. Secondary endpoints are usually not adjusted for multiple testing, so they support rather than confirm the primary finding.

Cmax for M1

• Endpoint type: Continuous: a mean value per participant, compared as a difference in means.
• Test: Unadjusted two-sample z-test for the difference in means, using the posted standard deviations.
• Result:
  • Caucasian 10 mg: mean 1.02 versus 1.23 on control; difference -0.21 (95% CI -0.41 to -0.01), standardized effect d = -0.91; z-test p = 0.041.
• Interpretation:
  • The 95% confidence interval excludes no difference, so the mean is statistically lower for Caucasian 10 mg than for the control. This is an unadjusted, secondary comparison, so it is suggestive rather than confirmatory.

AUC0-t for M1

• Endpoint type: Continuous: a mean value per participant, compared as a difference in means.
• Test: Unadjusted two-sample z-test for the difference in means, using the posted standard deviations.
• Result:
  • Caucasian 10 mg: mean 32.10 versus 37.10 on control; difference -5.00 (95% CI -12.75 to 2.75), standardized effect d = -0.57; z-test p = 0.206.
• Interpretation:
  • The 95% confidence interval includes no difference, so these data do not show a statistically significant difference between Caucasian 10 mg and the control. The interval gives the range of effects that remain compatible with the data.

AUC0-∞ for M1

• Endpoint type: Continuous: a mean value per participant, compared as a difference in means.
• Test: Unadjusted two-sample z-test for the difference in means, using the posted standard deviations.
• Result:
  • Caucasian 10 mg: mean 34.00 versus 38.70 on control; difference -4.70 (95% CI -12.80 to 3.40), standardized effect d = -0.51; z-test p = 0.256.
• Interpretation:
  • The 95% confidence interval includes no difference, so these data do not show a statistically significant difference between Caucasian 10 mg and the control. The interval gives the range of effects that remain compatible with the data.

The posted secondary summaries cover Cmax and area-under-the-curve measures for metabolite M1. The registry also lists outcomes for M1 and M3, including peak concentration, time to peak, and area-under-the-curve measures, but detailed arm summaries for every listed secondary outcome are not reported in the registry record. The available summaries broadly show higher mean M1 exposure measures at higher lomitapide dose cohorts in both populations. Japanese and Caucasian means are often relatively close in the posted summaries, though their ordering and separation vary by measure and dose.

This descriptive pattern provides context for the primary Cmax result: both relate to pharmacokinetic exposure, but the primary endpoint is parent lomitapide Cmax, whereas the secondary measures describe metabolites or accumulated exposure over time. Agreement in broad dose-related patterns across different measures can be informative descriptively, but it does not amount to a joint statistical test or validate a single population comparison. The primary result’s uncertainty remains specific to the 10 mg comparison of lomitapide Cmax.

The posted secondary comparisons are not accompanied by reported analyses in the registry record. Any unadjusted statistical results for multiple secondary endpoints would carry less weight than a prespecified primary analysis because repeated testing increases the chance of apparently notable findings arising by chance. The record does not report a multiplicity strategy, a hierarchy for secondary outcomes, or a confirmatory analysis plan. These results are best treated as exploratory descriptions that can motivate further study, not as independent proof of population differences or similarities.

Secondary outcomes registered for this trial, for reference (only those above were recalculated):

• Cmax for M1
• Tmax for M1
• AUC0-t for M1
• AUC0-∞ for M1
• t1/2 for M1
• Cmax for M3
• Tmax for M3
• AUC0-t for M3

9. Statistical Interpretation

10. Statistical Methods Explained

The primary outcome is continuous: each evaluable participant contributes a measured maximum plasma concentration. The registry summaries report the mean and standard deviation. A mean describes the group’s central value, while the standard deviation describes spread among observations within that group. Neither statistic alone shows the precision of a comparison; the confidence interval for the mean difference addresses uncertainty in that contrast.

What does the mean difference represent?

The posted primary comparison is an unadjusted difference between the Caucasian 10 mg group and the Japanese 10 mg group. Its estimate is -0.134 ng/mL. The negative sign follows the comparison’s direction: the Caucasian group mean is subtracted from the Japanese group mean in the stated order of Caucasian minus Japanese. A negative estimate therefore indicates a lower observed mean in the Caucasian group for this comparison. The estimate is a difference in group means, not a ratio or a percentage difference.

“Unadjusted” means the calculation is not reported as controlling for other participant characteristics or covariates. This simple comparison can describe the posted group summaries, but it may not address imbalance in factors that could influence concentrations. No adjusted model or covariate plan is reported in the registry record. The study’s randomization is a design feature; it does not turn this particular population-group comparison into a randomized assignment of ancestry.

What does the confidence interval add?

A confidence interval gives a range of values compatible with the observed data under the assumptions of the calculation. For the primary difference, the interval runs from -0.338 to 0.070 ng/mL. Its inclusion of zero means the data are compatible with no mean difference as well as with differences in either direction within the interval. It is not a guarantee that the true value lies in that range, and it does not show the probability that a particular value is true. The interval’s width also conveys that the estimate is uncertain.

How should the p-value be read?

The unadjusted p-value is 0.199. In general, a p-value describes how unusual data at least as incompatible with a specified null model would be if that model and the analysis assumptions held. It is not the probability that the null hypothesis is true, and it does not measure the size or clinical importance of a difference. Because the confidence interval includes zero, the p-value and interval give a consistent broad reading for this comparison. The registry record does not report a multiplicity adjustment or a sponsor-reported inferential analysis for this comparison.

Why are small groups important?

Endpoint group sizes are 10.0 in each 10 mg group and 6.0 in each higher-dose population group. Small group sizes can leave estimates sensitive to individual observations and can produce substantial uncertainty, particularly when observations vary. Standard deviations are not confidence intervals: they describe individual-level spread, whereas a confidence interval for a mean difference reflects uncertainty in the estimated contrast. The posted summaries do not include participant-level observations, so distribution shape, outliers, and alternative robust analyses cannot be assessed from the registry record.

What do the dose cohorts contribute?

The cohort means describe Cmax at the listed doses. Means increase across dose levels in both populations, but a pattern in descriptive means is not equivalent to a fitted dose-response model or a test of whether the dose-related pattern differs by population. No such model or test is reported in the registry record. The displayed group summaries are also not evidence that every participant’s concentration increased with dose; they summarize different groups at each dose.

General statistical practice distinguishes prespecified confirmatory analyses from exploratory comparisons. The registry record does not report the original statistical analysis plan, the planned primary contrast’s test procedure, or how analysis choices were made. Consequently, the unadjusted comparison should be read as a simple summary-based recalculation, not as a substitute for a complete protocol-defined analysis. There is no reported-analysis entry for the primary outcome in the record.

11. Confidence Intervals and Precision

For the primary comparison, the unadjusted mean difference is -0.134 ng/mL, and its 95% confidence interval extends from -0.338 to 0.070 ng/mL. This range includes zero and covers values on both sides of no difference. The estimate therefore does not pinpoint the direction of the underlying mean contrast with much certainty. The interval also indicates that the data do not rule out differences that may be meaningfully separated from the point estimate, although the registry record does not define a clinically important threshold for Cmax.

Precision depends on the amount of information in the comparison and the variability of the measurements. The primary groups each have 10.0 participants, and their standard deviations are 0.285 ng/mL and 0.166 ng/mL. The reported interval is a measure of uncertainty around the difference, not a range containing most individual participants’ concentrations. Individual values can be more dispersed than the uncertainty around a group mean difference suggests.

The unadjusted p-value of 0.199 is consistent with the interval’s inclusion of zero, but it should not replace reading the interval and estimate. A p-value does not show which differences remain compatible with the data, while the confidence interval gives that range in the measurement’s units. No adjusted interval, alternative model, or interval for a broader population-by-dose contrast is reported in the registry record. Precision should therefore be interpreted for this specific 10 mg comparison only, not generalized to all dose levels or pharmacokinetic outcomes.

12. Planning a Similar Trial: Sample Size

This is a planning illustration, not a re-evaluation of the original trial. It asks: if a new study wanted to detect a difference like the one observed, or a smaller one, how large would it need to be? It is deliberately not “observed power” of the finished trial, which is not a meaningful quantity.

The planning figures are participants per arm, not total events. They are illustrations based on the observed effect for the primary comparison, rather than the trial’s original enrollment design. The stated planning assumptions are a two-sided significance level of 0.05, equal allocation between the two arms, and a normal approximation. Each planning scenario targets a stated fraction of the observed effect.

For detecting 100% of the observed effect, the planning illustration gives 48 participants per arm for 80% power and 64 participants per arm for 90% power. For planning for 75% of the observed effect, it gives 85 participants per arm for 80% power and 114 participants per arm for 90% power. For planning for 50% of the observed effect, it gives 191 participants per arm for 80% power and 255 participants per arm for 90% power.

Power is the probability that a specified analysis would meet its statistical decision criterion if a particular effect were present and the planning assumptions held. The 80% and 90% columns therefore describe different target probabilities for detecting the assumed effect. A 90% target calls for more participants per arm than an 80% target in each listed scenario. Smaller effects are harder to distinguish from background variability, so planning for a smaller fraction of the observed effect requires more participants.

These values are planning illustrations, not observed power. They do not describe the probability that the completed study’s result is true, and they are not the original trial’s sample-size justification. The original design assumptions and sample-size justification are not reported in the registry record. The figures also depend on an effect estimated from the observed comparison, which may not be a reliable estimate of the effect that a future study would encounter.

13. How the Sample Size Is Derived

Power is the probability that a study of a given size rejects the null hypothesis when a specific true effect exists. It depends on four things: the effect to detect, the variability of the outcome, the significance level (here a two-sided α of 0.05, so z_1−α/2 = 1.960) and the desired power (z_1−β = 0.842 for 80% and 1.282 for 90%).

Formula

n is the number of participants in each arm, Δ is the difference in means to detect and σ is the common standard deviation.

Worked calculation for this trial

1. Observed difference Δ = -0.134; pooled standard deviation σ = 0.233.
2. n = 2 × (1.96 + 0.842)² × 0.233² / -0.134² = 47.6, rounded up to 48 participants per arm for 80% power.

The smaller-effect rows in the table above repeat the same calculation with the effect multiplied by 0.75 and 0.5 (for ratios, applied to the logarithm of the ratio).

R code

alpha <- 0.05
z_a   <- qnorm(1 - alpha / 2)          # two-sided
delta <- -0.134                      # observed difference in means
sigma <- 0.233217709447632                     # pooled standard deviation
n_per_arm <- function(power, frac = 1) {
  ceiling(round(2 * (z_a + qnorm(power))^2 * sigma^2 / (delta * frac)^2, 6))
}
for (f in c(1, 0.75, 0.5))
  cat(sprintf("%3.0f%% of observed effect: n per arm = %s (80%% power), %s (90%% power)\n", 100 * f,
              format(n_per_arm(0.80, f), big.mark = ","), format(n_per_arm(0.90, f), big.mark = ",")))

# Check against R's built-in function (t-based, so very slightly larger)
cat("power.t.test:", round(power.t.test(delta = delta, sd = sigma, power = 0.80)$n, 1), "\n")

# Simulation: exact two-sample t-test using simulated means and variances
set.seed(1760187)
n    <- n_per_arm(0.80)
reps <- 20000
m_diff <- rnorm(reps, delta, sigma * sqrt(2 / n))             # difference in sample means
s2     <- sigma^2 * rchisq(reps, 2 * (n - 1)) / (2 * (n - 1))   # pooled sample variance
tstat  <- m_diff / sqrt(s2 * 2 / n)
cat(sprintf("Simulated power at n = %s per arm: %.3f (%d replicates)\n", format(n, big.mark = ","), mean(abs(tstat) > qt(0.975, 2 * (n - 1))), reps))

Output from running the code

100% of observed effect: n per arm = 48 (80% power), 64 (90% power)
 75% of observed effect: n per arm = 85 (80% power), 114 (90% power)
 50% of observed effect: n per arm = 191 (80% power), 255 (90% power)
power.t.test: 48.5 
Simulated power at n = 48 per arm: 0.799 (20000 replicates)

The simulation draws many sets of group means and variances at the planned sample size and counts how often the two-sample t-test rejects the null. It should land close to the target power; at very small required sample sizes it can fall below it, because the normal approximation is rough there.

14. Multiplicity, Missing Data and Analysis Populations

The registry lists 27 outcome measures, while the posted record contains several secondary endpoint summaries and an unadjusted primary comparison. No analyses are listed as reported analyses. The statistical plan for choosing among outcomes, contrasts, or analysis populations is not reported in the registry record. In particular, it is not reported whether the primary contrast was prespecified in the same form as the posted comparison or whether secondary comparisons were subject to a multiplicity procedure.

Multiplicity matters when several outcomes or group comparisons are examined. In general, the more tests that are conducted, the greater the chance that at least one result will appear notable even if no underlying effect exists. Adjustment procedures, prespecified hierarchies, and clear identification of exploratory analyses are ways studies may address this issue. No such approach is reported, so unadjusted secondary p-values, if considered, should not be interpreted as confirmatory evidence. The primary unadjusted comparison also should not be presented as multiplicity-adjusted.

Missing-data handling is not reported in the registry record. The primary endpoint population is described as all subjects with evaluable concentrations, but the record does not describe how many participants lacked evaluable concentrations, why any were missing, or how missing concentration measurements were handled. It also does not report whether any imputation or sensitivity analyses were used. Without those details, the effect of missingness on the posted summaries cannot be assessed.

The record does not report a detailed analysis population definition beyond evaluable concentrations for the primary outcome. It is therefore not clear whether the analyses used all randomized participants, only participants who received study drug, or another population definition. The original analysis plan, model specifications, handling of protocol deviations, and rules for excluding observations are not reported in the registry record. These omissions limit assessment of whether the posted estimates follow a prespecified analysis and how robust they are to alternative choices.

15. Safety Results

The registry reports serious adverse events as affected participants divided by participants at risk.

Deaths

Other (non-serious) adverse events

Participants with at least one non-serious event at or above the registry's 0% reporting threshold.

Most frequent non-serious adverse event terms

The registry’s serious adverse event listings show zero affected participants in every listed group, and deaths are also recorded as zero in each group. The listed groups include placebo recipients and participants in the four lomitapide cohorts, separately for Japanese and Caucasian participants. The at-risk counts vary across groups, from 6 to 10 for the listed serious adverse event summaries. These are group-specific counts, not evidence that serious events are impossible or that the study can rule out uncommon harms.

Other adverse events are listed separately from serious adverse events. The counts affected vary across the groups, from 2 to 6 in the posted listings. These counts should be read in relation to each group’s at-risk count and the study’s limited size, not as direct estimates of comparative risk. The record does not provide event names in the serious-event listing, and the top serious-event terms list is empty. Further detail on event severity, duration, attribution, or timing is not reported in the registry record.

This phase I safety information describes events observed in the study groups. It does not establish a comprehensive safety profile or support conclusions about risks in other populations or treatment settings.

16. What the Result Does, and Does Not, Mean

The primary result addresses a narrow pharmacokinetic question: the difference in mean maximum observed lomitapide plasma concentration between Japanese and Caucasian participants in the 10 mg group. The posted means are 0.57 ng/mL and 0.436 ng/mL, respectively, and the unadjusted difference estimate is -0.134 ng/mL. Its 95% confidence interval, -0.338 to 0.070 ng/mL, includes zero. The result is therefore uncertain about the direction and size of the mean contrast.

This finding should not be translated into a claim that the populations have identical pharmacokinetics. A result that does not clearly distinguish a difference from zero can reflect limited precision as well as a small difference. Conversely, the observed mean difference does not establish a meaningful population effect. The registry does not report a clinical threshold for interpreting a Cmax difference, and Cmax is not itself a clinical outcome.

The study includes several dose cohorts and metabolite outcomes, but the primary inferential comparison posted for interpretation is the 10 mg group contrast. Descriptive dose patterns do not prove a dose-response relationship, and they do not establish whether population differences vary with dose. The findings also do not show whether any observed concentration pattern affects LDL-C, symptoms, or clinical events. The study’s stated purpose includes pharmacokinetics and pharmacodynamics, but the posted primary result is specifically a pharmacokinetic measure.

The results apply to the study groups and the endpoint measurements described in the registry record. They should not be assumed to apply to patients with a particular disease, to other demographic groups, or to clinical use outside this study. The record identifies healthy volunteers with elevated LDL-C and describes male participants; it does not report enough detail to characterize broader applicability. The safety listings likewise describe observed counts in these study groups and cannot settle the occurrence of uncommon events.

17. Why This Trial Matters Statistically

This trial raises a useful statistical question about how to compare pharmacokinetic measures across populations while also examining several dose levels. Its primary endpoint is a continuous concentration measure, so the mean difference, its confidence interval, and within-group variability all contribute to interpretation. Looking beyond whether a p-value crosses a threshold helps distinguish the estimated contrast from the uncertainty around it.

The posted result also illustrates why small phase I cohorts are best read with caution. The 10 mg comparison includes 10.0 participants per group, and the higher-dose population groups include 6.0 participants each. Such summaries can provide early information about observed concentrations, but they have limited precision for estimating population contrasts. A broad confidence interval should not be confused with proof of no difference, and a descriptive separation between means should not be treated as definitive evidence of one.

Multiple dose groups and multiple pharmacokinetic outcomes create an interpretive challenge. A consistent descriptive pattern may be scientifically interesting, but confirmation depends on prespecified comparisons and an analysis plan that addresses repeated testing. The registry record does not report those details. It is therefore important to separate the primary result from exploratory patterns and to avoid treating every endpoint as an independent confirmatory finding.

Finally, pharmacokinetic measures answer questions about concentrations and exposure, not by themselves questions about clinical benefit or harm. Clear statistical interpretation keeps those claims aligned with the endpoint actually measured. The trial’s value is in describing early concentration data and the uncertainty in a specific population comparison, not in resolving every question about dose response, population equivalence, or clinical outcomes.

18. Limitations

• The posted summary statistics are the only data these results rest on; patient-level data, full protocols and statistical analysis plans are not available.
• Recalculated results are simple, unadjusted calculations from posted summaries. They do not replace the sponsor's prespecified analysis.

The primary inferential comparison is limited to the 10 mg cohort. Although arm-level means are posted for higher dose levels, an inferential comparison across populations at those levels is not reported in the registry record. The available summaries cannot establish whether the difference between populations changes with dose or whether a statistical interaction is present.

Group sizes are small, and the endpoint population includes subjects with evaluable concentrations. The number and characteristics of participants without evaluable measurements, if any, are not reported in the registry record. Participant-level concentrations and distributional summaries beyond means and standard deviations are also unavailable in the record, limiting assessment of outliers, skewness, and robustness.

The registry does not report the original protocol’s sample-size rationale, detailed statistical analysis plan, randomization method, or prespecified multiplicity approach. It also does not describe missing-data procedures, covariate adjustment, or sensitivity analyses. These omissions make it difficult to determine how the posted summaries relate to planned analyses and how conclusions might change under other reasonable methods.

Generalizability is restricted by the registry’s description of healthy male Japanese and Caucasian volunteers with elevated LDL-C. The record does not provide detailed characteristics that would show how closely these participants resemble broader clinical populations. The listed schedule and endpoint refer to measurements through 168 hours postdose on Day 7, but the record does not give enough information to characterize the full dosing and follow-up procedures. The safety counts are likewise limited by the small groups and the lack of event-level detail.

19. Related Tutorials

20. Related Statistical Calculators

21. Sources

• ClinicalTrials.gov: Phase I Study of the Safety, Tolerability, PK & PD of Lomitapide in Japanese and Caucasian Subjects With Elevated LDL-C — NCT01760187.
• Registry record last updated 2018-11-20; status last verified 2018-11.
• Results first posted 2018-11-20.
• Data retrieved from ClinicalTrials.gov on 2026-11-09.
• Group sizes, means, event counts and sponsor-reported p-values are reproduced as posted. Effect estimates, confidence intervals and p-values not attributed to the sponsor are independently calculated from the posted summary statistics.

22. Record Summary

NCT01760187 is a completed phase I randomized, double-blind, placebo-controlled, parallel study with quadruple masking. It evaluated orally administered lomitapide in healthy male Japanese and Caucasian volunteers with elevated LDL-C through single ascending dose and multiple ascending dose cohorts. The registry records enrollment of 72 and lists 10 mg, 20 mg, 40 mg, and 60 mg cohorts.

The primary endpoint was maximum observed lomitapide plasma concentration. At 10 mg, the posted group means were 0.57 ng/mL for Japanese participants and 0.436 ng/mL for Caucasian participants. The unadjusted mean difference was -0.134 ng/mL, with a 95% confidence interval from -0.338 to 0.070 and an unadjusted p-value of 0.199. The interval includes zero and indicates uncertainty in the estimated contrast.

Descriptive summaries show increasing mean concentrations across dose cohorts, but the registry does not report inferential comparisons for every dose or a detailed analysis plan. Serious adverse event and death counts were zero in the listed groups; other adverse events were recorded. The posted findings describe early pharmacokinetic and safety observations and do not establish clinical effects.