Formula uncertainty versus surface-area model error

Formula uncertainty versus surface-area model error separates precision in evaluating a body-size formula from adequacy of that formula for an individual's actual body surface area. Repeating height and mass measurements can reduce their sampling uncertainty without making the predicted anatomical surface exact.

The Mosteller formula, documented with centimetre and kilogram inputs in the VA manual, is $\hat{S}=\sqrt{H_{\mathrm{cm}}{M}_{\mathrm{kg}}/3600}{\mathrm{m}}^2$.^[ref] An original measurement model can instead write $S_{\mathrm{true}}=f(H,M;\theta )+D$, where $\theta$ represents fitted coefficients and $D$ residual model discrepancy. Variation in body shape is not represented by improved arithmetic alone.

For small independent input errors with fixed coefficients,Coefficient uncertainties, correlations and model discrepancy are additional terms when significant. The GUM explicitly requires a measurement model to include relevant corrections and quantities reflecting incomplete knowledge.^[ref]

For stipulated prediction $2.00{\mathrm{m}}^2$, input-related standard uncertainty $0.02{\mathrm{m}}^2$ and independent zero-mean discrepancy uncertainty $0.10{\mathrm{m}}^2$, the combined value is $\sqrt{0.02^2+0.10^2}\approx 0.102{\mathrm{m}}^2$. Reducing only the input term tenfold gives approximately $0.100{\mathrm{m}}^2$, illustrating a repeatability floor from surface-area model discrepancy. These are constructed uncertainties, not published performance limits. A known nonzero model bias calls for correction; assigning a zero-mean random term does not remove it.

Normalization can transmit the discrepancy into another quantity. For fixed measured cardiac output $Q$, the ratio of $Q/\hat{S}$ to $Q/S_{\mathrm{true}}$ is $S_{\mathrm{true}}/\hat{S}$. A stipulated true area 2.0 and predicted area $1.8{\mathrm{m}}^2$ therefore increases the indexed result by about 11.1%. Extra displayed digits do not resolve the anatomical mismatch.

A validation experiment compares predictions with independently characterized surface measurements over the intended range of body shapes and sizes, retaining uncertainty in the reference method. Report input repeatability, coefficient estimation, average bias and residual spread separately rather than interpreting them all as one source of error.

A repeatability floor from surface-area model discrepancy is the remaining uncertainty when repeated measurements reduce input noise but reuse the same imperfect anatomical predictor. Repeating height and mass measurements does not independently redraw the relationship between those quantities and one person's actual body surface area.

An original local model writes prediction $X_i=S+D+{ϵ}_i$, where $S$ is the true area, $D$ a shared model discrepancy and ${ϵ}_i$ independent repeat noise. Represent uncertainty about $D$ by variance ${\tau }^2$ and repeat noise by variance ${\sigma }^2$, assuming independence between them. For the mean of $n$ repeats,The correlation is a consequence of reusing the same discrepancy. The GUM requires significant common-input correlations to be included and permits additional model quantities for incomplete knowledge.^[ref]

For stipulated $\sigma =0.04{\mathrm{m}}^2$ and $\tau =0.08{\mathrm{m}}^2$, the mean's standard uncertainty is about $0.0894{\mathrm{m}}^2$ after one reading, $0.0825{\mathrm{m}}^2$ after four and $0.0801{\mathrm{m}}^2$ after one hundred. The lower limit is $0.08{\mathrm{m}}^2$ in this model, not zero. These values illustrate the distinction rather than report a measured error distribution for the Mosteller formula.

Repeat-count targets under shared model error make a useful planning calculation. Requiring the repeat-noise variance to be at most a fraction $\eta$ of the shared variance gives $n\ge {\sigma }^2/(\eta {\tau }^2)$. With the chosen values and $\eta =0.01$, 25 repeats suffice; further repetition changes the total uncertainty little while leaving the dominant model term intact.

The shared term need not fluctuate between actual readings. For a fixed person, an unknown prediction bias can remain fixed while repeatability looks excellent. Its distribution represents uncertainty or variation across the validation population, not a physical mechanism that changes body shape on each measurement.

A useful validation therefore combines repeat measurements with independent reference-area evidence across an appropriate range of individuals. Distinguish within-person repeatability, shared calibration effects and model residuals. If a systematic bias is established, correcting it is a separate step from describing residual uncertainty.

Repeat-count targets under shared model error choose how many independent readings are worth averaging when part of the uncertainty is common to every repeat. In the local measurement model $X_i=S+D+{ϵ}_i$, let the shared discrepancy have variance ${\tau }^2$, and the independent repeat noise have variance ${\sigma }^2$. Assuming the two components are independent,The common term produces covariance between readings and survives averaging. The GUM's correlated-input rule retains precisely such shared contributions.^[ref]

For a desired total standard uncertainty $u_{\ast }>\tau$, solve the inequality before choosing the integer repeat count:If $\sigma >0$, a target equal to $\tau$ cannot be attained with any finite repeat count, and a target below $\tau$ is unattainable within this model. This is the feasibility threshold for averaging under shared uncertainty.

In an original body surface area example, take $\sigma =0.04{\mathrm{m}}^2$ and $\tau =0.08{\mathrm{m}}^2$. A target $u_{\ast }=0.081{\mathrm{m}}^2$ needs ten repeats; $u_{\ast }=0.0801{\mathrm{m}}^2$ needs one hundred. A target of $0.079{\mathrm{m}}^2$ instead requires reducing the shared component or changing the model. Merely collecting more readings is insufficient.

Two relative criteria illustrate why the target must be explicit. Requiring repeat-noise variance to be at most $\eta {\tau }^2$ gives $n\ge {\sigma }^2/(\eta {\tau }^2)$: at $\eta =0.01$, 25 repeats suffice. Requiring total standard uncertainty within 1% of its floor instead giveswhich needs 13 repeats with the same stipulated numbers. A 1% variance criterion and a 1% standard-uncertainty criterion are different requirements.

The calculation assumes independent repeat noise and a justified shared-error model. Repeated observations alone cannot estimate an individual fixed discrepancy; independent reference measurements or a suitable validation population are needed to constrain it.

A feasibility threshold for averaging under shared uncertainty is the smallest uncertainty that repetition can approach while a common uncertain contribution remains unchanged. In the measurement model $X_i=S+D+{ϵ}_i$, suppose the shared term has variance ${\tau }^2$ and independent repeat noise has variance ${\sigma }^2$. ThenFor $\sigma >0$, every finite repeat count has $u_n>\tau$, although $u_n$ tends to $\tau$ as $n$ grows. A target below the floor is infeasible within this model, and a target exactly at it needs an infinite count. The GUM's correlated-input propagation explains why a common contribution is retained rather than divided by the repeat count.^[ref]

Approaching the floor has a quantifiable cost. To obtain $u_n\le \tau (1+\delta )$ with $\tau >0$, solveFor small positive $\delta$, the required count grows approximately as $1/\delta$. With stipulated $\sigma =0.04{\mathrm{m}}^2$ and $\tau =0.08{\mathrm{m}}^2$, getting within 1% of the floor needs 13 repeats, within 0.1% needs 125, and within 0.01% needs 1,250. These are planning examples for body surface area prediction, not observed clinical performance limits.

Precision limits of weighting correlated repeats show why a clever average cannot remove the common term for free. A linear estimate $\hat{S}={\sum }_i{w}_i{X}_i$ that preserves the unknown $S$ requires ${\sum }_i{w}_i=1$. The shared discrepancy therefore enters with coefficient one as well, givingThe inequality follows from ${\sum }_i{w}_i^2\ge 1/n$; equal weights attain it under the stipulated equal independent repeat-noise variances. Negative weights do not evade the floor while preserving the signal coefficient.

Reaching a lower uncertainty requires additional information or a changed measurement model that reduces the common contribution. Repeating a validation method with genuinely independent reference errors can supply different information, whereas repeating one person's height and mass measurements does not redraw that person's model discrepancy. A known bias calls for a correction, not a claim that averaging will make it disappear.^[ref]

Precision limits of weighting correlated repeats describes what a weighted mean can achieve when repeated observations share an uncertain contribution. Supposewith independent, zero-mean repeat errors ${ϵ}_i$ independent of $D$. An estimate $\hat{S}={\sum }_i{w}_i{X}_i$ must satisfy ${\sum }_i{w}_i=1$ to preserve the unknown signal $S$. The shared contribution then has coefficient one as well:This is a special case of correlated-input measurement uncertainty propagation. The covariance matrix is $\Sigma ={\tau }^{2}11^{\mathsf{T}}+\mathrm{diag}({\sigma }_i^2)$; omitting its off-diagonal terms would incorrectly treat the common uncertainty as independently redrawn.^[ref]

The Cauchy-Schwarz inequality gives a sharp bound:Equality occurs for inverse-variance weighting,For equal repeat variances this reduces to equal weights and $u_{\min }^2={\tau }^2+{\sigma }^2/n$. Allowing negative weights cannot improve this bound within the stated model.

For an original body surface area prediction example, take shared standard uncertainty $\tau =0.050{\mathrm{m}}^2$ and two repeat-noise values ${\sigma }_1=0.040{\mathrm{m}}^2$ and ${\sigma }_2=0.080{\mathrm{m}}^2$. The optimal weights are $0.8$ and $0.2$, giving $u_{\min }=\sqrt{0.0025+0.00128}\approx 0.0615{\mathrm{m}}^2$. Equal weights give approximately $0.0671{\mathrm{m}}^2$. Weighting helps, but it does not erase the shared $0.050{\mathrm{m}}^2$ contribution. These values are stipulated, not clinical performance data.

For a fixed individual, $D$ can represent an unknown constant model discrepancy rather than a fluctuation between readings. No weights summing to one can distinguish that discrepancy from $S$, because both enter every observation identically. Independent reference information or a better anatomical measurement model is required to constrain it. If the residual errors themselves have further covariance, their full matrix replaces the diagonal repeat-noise model; the displayed inverse-variance weights no longer follow automatically.