Int. J. Metrol. Qual. Eng.
Volume 7, Number 4, 2016
|Number of page(s)||8|
|Published online||28 October 2016|
Control chart limits based on true process capability with consideration of measurement system error
Laboratoire de Mécanique, Matériaux et Procédés (LR99ES05), ENSIT, University of Tunis,
5 Av Taha Hussein Montfleury,
1008 Tunis, Tunisia
2 ENIM, University of Monastir, Av Ibn Eljazzar, 5019 Monastir, Tunisia
⁎ Corresponding author: email@example.com
Accepted: 16 September 2016
Shewhart X̅ and R control charts and process capability indices, proven to be effective tools in statistical process control are widely used under the assumption that the measurement system is free from errors. However, measurement variability is unavoidable and may be evaluated by the measurement system discrimination ratio (DR). This paper investigates the effects of measurement system variability evaluated by DR on the process capability indices Cp and Cpm, on the expected non conforming units of product per million (ppm), on the expected mean value of the Taguchi loss function (E(Loss)) and on the Shewhart charts properties. It is shown that when measurement system variability is neglected, an overestimation of ppm and underestimation of E(Loss) are induced. Moreover, significant effects of the measurement variability on the control chart properties were made in evidence. Therefore, control charts limits calculation methods based on process real state were developed. An example is provided in order to compare the proposed limits with those traditionally calculated for Shewhart X̅, R charts.
Key words: process capability indices / expected non conforming units of product per million (ppm) / mean value of Taguchi loss function E(Loss) / measurement system discrimination ratio / Shewhart X̅, R control chart parameters
© EDP Sciences, 2016
Quality is actually an ongoing challenge facing manufacturing industry. Hence, manufacturers have resorted to statistical process control (SPC) for monitoring, maintaining and improving the performance of process to produce parts conforming to their customer's expectations. The two main tools of SPC are control charts and process capability analysis. The popular Shewhart X̅ and R charts are extensively applied to graphically controlling the process mean and range variations .
On the other hand, the process capability indices are commonly used in process analysis to numerically exhibit how the process is performing relative to specification limits. Nevertheless, process capability evaluation and control charts implementation require data obtained through measurements. Since measurement system variability cannot be avoided , it must be taken into account before and while assessing process capability and calculating control charts limits. DR was developed to compare the former variability to the process unevenness and employed as a measurement system acceptability criterion [2–4].
The majority of research works related to control chart assumed that the used measurement system is perfect and free from errors. Therefore, control limits are calculated based on the total variability including the real process variability and the measurement system variability. In some cases, the real process state is much better than the observed one and the observed total variation is mainly governed, by the variability of the measurement system rather than the process. If this fact is not considered, unreliable decisions about the process may be made . The purpose of this investigation is to contribute filling this gap of knowledge by developing X̅ and R control charts limits for the real process state. The paper is divided into two major parts. In the first part, effects of the measurement system variability on the commonly used process capability indices, Cp and Cpm are discussed. In the second part, calculation methods for Shewhart X̅, R control charts limits are developed to consider the real process state.
In the case of stable, normally distributed process, having two sided symmetric specification limits and the mean of the distribution is centred at the middle of the specifications, Cp is defined as below : (1) where σp is the real process standard deviation, USL and LSL are the upper and lower specification limits, respectively and d is the half specification width (d = (USL−LSL)/2). The index Cp measures the process ability to manufacture products that meet the specification limits.
Consequently, a usual problem tackled in practice consisting on how to distinguish between the measurement system and the process variabilities. Therefore, it is essential to assess the measurement system variability σm by conducting an analysis as recommended by the Automotive Industry Action Group (AIAG) standard . This standard, defines the measurement system discrimination ratio (DR) as follows: (3)
DR describes how many classifications can be reliably distinguished by the measurement system . The value of DR is compared to a threshold value to make the appropriate decision about the measurement system acceptability. Wheeler and Lyday  stated that while DR more than 4 is acceptable, DR less than 2 indicates that the measurement system is inadequate to evaluate the process variability. When DR ranges between 2 and 4, the measurement system may be accepted for some specific applications.
As for the process capability evaluation, in practice, a capability analysis yields to an observed capability index (Cp,Obs) integrating the total variability (σt) rather than the process true index (Cp,True). Cp,Obs is expressed as follows: (4)
Based on equation (3), Cp,True can be expressed as function of DR as: (6)
Equation (6) shows that low values of DR result on wide differences between Cp,Obs and Cp,True.
Taguchi  identified another source of process variability related to decentring. He stated that as the measured product characteristic (X) departs from a predefined target value (T) an economic loss is incurred. Hence, to express this loss, he proposed the following quadratic loss function : (7) where k expresses the quality loss coefficient. This coefficient may be deduced from a replacement/repair cost function A0 = Loss(T ± d) pertaining to a nonconforming part and expressed as below [10,11],
The expected mean value of the Taguchi loss function can be expressed as follow : (10) where (μ) is the process mean.
Based on this concept, Chan et al.  introduced the Taguchi capability index Cpm that is directly related to the former quadratic loss function of the measured feature. In the case of stable, normally distributed process, having two sided specification limits and a target value T that can be different from the process mean μ, Cpm is defined as below : (11)
The index Cpm emphasizes the ability of the process to cluster around the target. Hence, it takes into account both the process decentring and variability . In practice, the measured index is denoted as the observed one Cpm,Obs and defined as: (12)
As σp is unknown, it can be deduced from the observed capability index Cp,Obs (Eq. (6)) as follow: (15)
Process capability index Cpm,True can be used to draw conclusions about process fallouts expressed in expected non conforming units of ppm. In recent work, Perakis and Xekalaki  defined the proportion of conformance of a process (P) while neglecting the measurement system error (Cpm,Obs = Cpm,True) by the following expression: (16)
However, as indicated above, the measurement system error cannot be neglected and equation (17) will be corrected in the followings to consider the impact of the measurement system variability on ppm. (18)
In order to highlight the effects of the measurement system variability on ppm, the same example used in reference  (see Appendix) and initially employed by Grant and Leavenworth  is utilized to compute ppm for different values of DR (Tab. 1). Data are pertaining to measurements of diameters on shafts. In this paper, as international unit system is used, data of reference  that are originally in inch were converted in mm. The lower and the upper specification limits are set to 10.22 mm (0.4024 in) and 10.28 mm (0.4050 in) respectively, and target value is assumed to be equal to 10.248 mm (0.4035 in) and the process mean is equal to 10.245 mm (0.403355 in). The observed process capability indices calculated using the data set are Cp,Obs = 1.228 and Cpm,Obs = 1.135 (Eqs. (4) and (12)). If measurement error is neglected then equation (17) can be used to compute ppm. The calculated value in this case is ppm = 3415 units (Tab. 1).
As shown in Table 1, increasing the measurement system DR suggests that the process capability is evaluated with a measurement system with lower variability. Therefore, the total variation tends to be equal to the process variation. Hence, Cpm,Obs becomes closer to Cpm,True and consequently, the gap between the expected ppm calculated using the observed Cpm,Obs and using Cpm,True becomes much narrow. It is important to notice that the expected ppm when using a measurement system with a DR = 4 (value recommended by the AIAG) is equal to 1989. In this case, the expected ppm is overestimated to about 41% of it is real value.
Based on data of the example introduced earlier, E(Loss) is firstly calculated while neglecting measurement variability (Cpm,True = Cpm,Obs) and secondly when considering this variability for different values of DR. The replacement/repair cost A0 is supposed to be equal to 40 × 103$, hence the quality loss coefficient k [$/mm2] is equal to 44.44 × 106$/mm2 . Results are summarized in Table 2.
From Table 2, it can be observed that E(Loss) becomes higher as DR increases. This can be explained by the fact that measurement variability overlaps the real variability of the process. Indeed, by using a measurement system with smaller DR, practitioner assesses observed process capability that is lower than the true one and E(Loss) value is underestimated in this case.
Values of Cpm,True function of DR with associated values of expected ppm.
Values of Cpm,Obs and Cpm,True with associated values of E(Loss)$.
When the controlled quality characteristic is a variable, X̅ and R control charts are commonly used. These charts are constructed from data collected by sampling. While X̅ control chart is used for monitoring the process mean, R chart is used to supervise the process variability.
Control limits for the X̅ chart are formulated as below : (20) (21) where X̿ is the process mean and σX̅p is the standard deviation of X̅i,i = 1,…,m (m number of samples) without considering the measurement variability.
By referring to equation (6), σX̅p can be given as: (24)
In the followings, the effect of the discrimination ratio DR on the control chart limits calculation will be discussed under the main condition of fixed value of Cp,Obs (i.e. Cp,Obs = 1.22).
Figure 1 shows the relationship between the discrimination ratio DR and the normalized ratio (σX̅p/d) for different sample sizes n. This figure clearly shows that the effect of DR is widely conditioned by the sample size. Indeed, the measurement system variability evaluated by DR has no significant effect on the normalized ratio (σX̅p/d) for high values of the sample size (i.e. n = 320). In these cases, no particular correction is required for control charts limits. Meanwhile, for small sample size corrections must be carried out to take into account the variability of the measurement system. According to plots of Figure 1, the recommended value of DR by the AIAG (DR = 4), seems to be an acceptable threshold value from which the measurement system can be applied in SPC.
Moreover, this figure shows that even measurement systems with DR lower than the recommended threshold value, that are unacceptable according to AIAG standard, can be used to control and monitor the process after introducing the required corrections to chart limits.
These corrections can be expressed as below.
For the R chart:
By referring to the equation (24), the average range can be expressed as: (31)
Figure 2 shows the variation of samples average range R̅ as function of DR for fixed value of Cp,Obs (i.e. Cp,Obs = 1.22). This figure shows that similarly to the X̅ chart, the samples average range R̅ is dependent on the sample size and the measurement system discrimination ratio DR has a significant effect on the R̅ chart characteristics. This effect is seen to be as important as DR is low.
Constants D4 and D3 depend on sample size n .
Relationship between DR and the ratio (σX̅p/d) (Cp,Obs = 1.22).
Variation of R̅ depending on DR (Cp,Obs = 1.22).
The machined shafts example described earlier is used to put in evidence the importance of the proposed corrections that must be made for control charts limits calculation depending on the measurement system discrimination ratio DR. In this example, sampling is made using a sample size n = 5. Therefore, d2 = 2.326, D3 = 0 and D4 = 2.114 (for details see reference ).
Results of limits calculations are given in Table 3 for DR = 2, 4 and 9. In this table, the traditional control limits refer to limits calculation under the assumption of perfect measurement system (σX̅p ≈ σX̅p).
Corrected control limits in cases of DR = 2, 4 and 9 and uncorrected control limits are plotted in Figure 3a and b for X̅ and R control chart, respectively. In Figure 3a, in order to reduce the scale effect between a sample mean (X̅i, in the order of 10.2xx mm) and the difference between two means ((X̅i − X̅j), in the order of 0.0xx mm), X̅ chart is plotted using (X̅i − 10.200) mm format.
Control charts given by Figure 3 show that the widest upper and lower control limits correspond to the traditional ones followed by limits calculated for DR = 9 and thereafter DR = 4. This is because uncorrected limits consider both process and measurement system variabilities. For a constant value of observed capability, the contribution of the measurement system on the total observed variability increases for low values of DR. This means that the observed variability is governed by the measurement system rather than the process variability. Therefore, control charts parameters must be corrected to avoid misinterpretation of the process state and the consequent wrong decisions.
Comparison between traditional and corrected control limits for different values of DR (Cp,Obs = 1.22).
(X̅, R) Shewhart charts plotted using corrected (DR = 2, 4 and 9) and traditional limits. (a) X̅ chart, (b) R chart.
The work presented in this paper deals with issue related to the effects of measurement system variability evaluated by the discrimination ratio DR on the process capability indices Cpand Cpm, on the expected non conforming units of ppm, on the expected mean value of the Taguchi loss function (E(Loss)) and on the Shewhart X̅ and R charts properties. It was found that DR has significant effects on these process characterization parameters and that the accurate calculation of these parameters must consider the measurement system variability. Therefore, new equations were developed to integrate these effects. When exploring these equations, it was found that differences between the observed uncorrected parameters and the corrected ones are as significant as the discrimination ratio DR is low.
Process capability indices and control charts are appropriate tools to evaluate process performances and monitor its outputs. However, quality practitioner may not pay attention to measurement system variability when evaluating and controlling the process. This paper shows that the measurement system variability has a significant impact on the calculation of the capability indices Cp and Cpm, on the expected non conforming units of ppm, on the expected mean value of the Taguchi loss function E(Loss) and on the control charts parameters. For this purpose, new calculation methods to evaluate the real process state were developed to help avoiding wrong analysis and the consequent unreliable decisions.
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Cite this article as: Souha Ben Amara, Jamel Dhahri, Nabil Ben Fredj, Control chart limits based on true process capability with consideration of measurement system error, Int. J. Metrol. Qual. Eng. 7, 401 (2016)
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