CCHART Statement: SHEWHART Procedure

Constructing Charts for Numbers of Nonconformities (c Charts)

The following notation is used in this section:

u

expected number of nonconformities per unit produced by the process

$u_{i}$

number of nonconformities per unit in the ith subgroup

$c_{i}$

total number of nonconformities in the ith subgroup

$n_{i}$

number of inspection units in the ith subgroup. Typically, $n_{i} = 1$ and $u_ i=c_ i$ for c charts. In general, $u_{i}=c_{i}/n_{i}$.

$\bar{u}$

average number of nonconformities per unit taken across subgroups. The quantity $\bar{u}$ is computed as a weighted average:

\[  \bar{u} = \frac{n_{1}u_{1} + \cdots + n_{N}u_{N}}{n_{1} + \cdots + n_{N}} = \frac{c_{1} + \cdots + c_{N}}{n_{1} + \cdots + n_{N}}  \]

N

number of subgroups

$\chi ^{2}_{\nu }$

has a central $\chi ^{2}$ distribution with $\nu $ degrees of freedom

Plotted Points

Each point on a c chart represents the total number of nonconformities ($c_{i}$) in a subgroup. For example, Figure 17.24 displays three sections of pipeline that are inspected for defective welds (indicated by an X). Each section represents a subgroup composed of a number of inspection units, which are 1000-foot-long sections. The number of units in the ith subgroup is denoted by $n_{i}$, which is the subgroup sample size. The value of $n_{i}$ can be fractional; Figure 17.24 shows $n_{3}=2.5$ units in the third subgroup.

Figure 17.24: Terminology for c Charts and u Charts

Terminology for Charts and Charts


The number of nonconformities in the ith subgroup is denoted by $c_{i}$. The number of nonconformities per unit in the ith subgroup is denoted by $u_{i}=c_{i}/n_{i}$. In Figure 17.24, the number of welds per inspection unit in the third subgroup is $u_{3}=2/2.5=0.8$.

A u chart created with the UCHART statement plots the quantity $u_{i}$ for the ith subgroup (see UCHART Statement: SHEWHART Procedure). An advantage of a u chart is that the value of the central line at the ith subgroup does not depend on $n_{i}$. This is not the case for a c chart, and consequently, a u chart is often preferred when the number of units $n_{i}$ is not constant across subgroups.

Central Line

On a c chart, the central line indicates an estimate for $n_{i}u$, which is computed as $n_{i}\bar{u}$. If you specify a known value ($u_{0}$) for u, the central line indicates the value of $n_{i}u_{0}$.

Note that the central line varies with subgroup sample size $n_{i}$. When $n_{i}=1$ for all subgroups, the central line has the constant value $\bar{c} = (c_{1} + \cdots + c_{N})/N$.

Control Limits

You can compute the limits in the following ways:

  • as a specified multiple (k) of the standard error of $c_{i}$ above and below the central line. The default limits are computed with k = 3 (these are referred to as $3\sigma $ limits).

  • as probability limits defined in terms of $\alpha $, a specified probability that $c_{i}$ exceeds the limits

The lower and upper control limits, LCLC and UCLC respectively, are given by

\begin{eqnarray*}  \mbox{LCLC} &  = &  \mbox{max}\left(n_{i}\bar{u} - k\sqrt {n_{i}\bar{u}}\;  ,0 \right) \\ \mbox{UCLC} &  = &  n_{i}\bar{u}+ k\sqrt {n_{i}\bar{u}} \end{eqnarray*}

The upper and lower control limits vary with the number of inspection units per subgroup $n_{i}$. If $n_ i=1$ for all subgroups, the control limits have constant values.

\begin{eqnarray*}  \mbox{LCLC} &  = &  \mbox{max}\left(\bar{c} - k\sqrt {\bar{c}}\;  ,0 \right) \\ \mbox{UCLC} &  = &  \bar{c}+ k\sqrt {\bar{c}} \end{eqnarray*}

An upper probability limit UCLC for $c_{i}$ can be determined using the fact that

\[  \begin{array}{ll} P\{ c_{i} > \mbox{UCLC}\}  &  = 1 - P\{ c_{i} \leq \mbox{UCLC} \}  \\ &  = 1 - P\{ \chi ^{2}_{2(\! {\scriptstyle \text {UCLC}}+1)} \geq 2n_{i}\bar{u}\}  \end{array}  \]

The upper probability limit UCLC is then calculated by setting

\[  1 - P\{ \chi ^{2}_{2(\! {\scriptstyle \text {UCLC}}+1)} \geq 2n_{i}\bar{u}\}  = \alpha /2 \]

and solving for UCLC.

A similar approach is used to calculate the lower probability limit LCLC, using the fact that

\[  \begin{array}{ll} P\{ c_{i} < \mbox{LCLC}\}  &  = P\{ c_{i} \leq \mbox{LCLC}-1\}  \\ &  = P\{ \chi ^{2}_{2(\! {(\scriptstyle \text {LCLC}}-1)+1)} > 2n_{i}\bar{u}\}  \\ &  = P\{ \chi ^{2}_{2\scriptstyle \text {LCLC}} > 2n_{i}\bar{u}\}  \end{array}  \]

The lower probability limit LCLC is then calculated by setting

\[  P\{ \chi ^{2}_{2\scriptstyle \text {LCLC}} > 2n_{i}\bar{u}\}  = \alpha /2 \]

and solving for LCLC. This assumes that the process is in statistical control and that $c_{i}$ has a Poisson distribution. For more information, refer to Johnson, Kotz, and Kemp (1992). Note that the probability limits vary with the number of inspection units per subgroup ($n_ i$) and are asymmetric about the central line.

If a standard value $u_{0}$ is available for u, replace $\bar{u}$ with $u_0$ in the formulas for the control limits. You can specify parameters for the limits as follows:

  • Specify k with the SIGMAS= option or with the variable _SIGMAS_ in a LIMITS= data set.

  • Specify $\alpha $ with the ALPHA= option or with the variable _ALPHA_ in a LIMITS= data set.

  • Specify a constant nominal sample size $n_{i} \equiv n$ for the control limits with the LIMITN= option or with the variable _LIMITN_ in a LIMITS= data set.

  • Specify $u_{0}$ with the U0= option or with the variable _U_ in a LIMITS= data set.