Violation in Mixing
Violation in Mixing
Violation in Mixing
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174 Analysis of the time-dependent �È -violat<strong>in</strong>g asymmetry <strong>in</strong> � � � � decays<br />
Parameter Run 1 Run 2 MC<br />
� ÓÖ� � � ¦ � � � ¦ � � � � ¦ � �<br />
� ÓÖ� �� � ¦ � �� ¦ � � ��� ¦ �<br />
�Ø��Ð � �� ¦ � � � �� ¦ � � � � ¦ �<br />
�Ø��Ð � � ¦ � � � ¦ � � � � ¦ � ��<br />
�Ø��Ð �� ¦ � � �� � ¦ � �� ���� ¦ � �<br />
�ÓÙØ � �� ¦ � � � �� ¦ � � � ¦ � �<br />
�ÓÙØ (fixed) � (fixed) � (fixed)<br />
�ÓÙØ ����� ¦ � �� � ¦ � �� �� �� ¦ ����<br />
Table 7-7. Parameters for the triple-Gaussian background ¡Ø resolution function Ê ��� <strong>in</strong> on-resonance<br />
and cont<strong>in</strong>uum Monte Carlo samples. Separate parameterizations are used for Run 1 and Run 2. Means and<br />
resolutions are <strong>in</strong> Ô×.<br />
component, even for events. We therefore choose to parameterize the distribution as the sum of three<br />
Gaussians: core, tail, and outlier, with the same parameters for ��, Ã�, and Ãà background. Attempt<strong>in</strong>g<br />
to <strong>in</strong>corporate event-by-event errors leads to unstable parameterizations, therefore, we do not make use of<br />
the ¡Ø error.<br />
The Gaussian parameters are obta<strong>in</strong>ed from an unb<strong>in</strong>ned maximum likelihood fit to the on-resonance sideband<br />
sample, with the outlier mean fixed to Ô×. Figure 7-3 shows the fit result for Run 1 and Run 2 data.<br />
Table 7-7 lists the fitted parameters. The � ��� for the triple-Gaussian fit is �� <strong>in</strong> Run 1 and �� <strong>in</strong><br />
Run 2. The Kolmogorov test returns a probability of �� for both Run 1 and Run 2. There is a significant<br />
negative bias <strong>in</strong> ���Р<strong>in</strong> Run 1 and a positive bias <strong>in</strong> Run 2. The orig<strong>in</strong> of the shifts is not understood, but it<br />
is accounted for <strong>in</strong> the systematic error (Sec. 7.10).<br />
Several cross-checks have been performed to validate the ¡Ø parameterization. Figure 7-4 shows the onresonance<br />
side-band data compared to a parameterization obta<strong>in</strong>ed <strong>in</strong> the fit region. In this fit the signal<br />
and background yields are determ<strong>in</strong>ed from Ñ�Ë, ¡�, �, and � simultaneously with the background ¡Ø<br />
parameters. For the signal, we use the same resolution function as the ×�Ò ¬ analysis [70]. Good agreement<br />
is found between the parameters obta<strong>in</strong>ed from the fit region and side-band data.<br />
In order to justify us<strong>in</strong>g an average of all species, we fit the side-band data with separate parameters for each<br />
species. We f<strong>in</strong>d no difference between the �� and Ã� parameters, and only small differences <strong>in</strong> the ÃÃ<br />
sample. These differences are probably due to the significant correlation between Gaussian parameters and<br />
the fewer number of ÃÃ events <strong>in</strong> the sample (cf. Table 7-5). The average fit results (Table 7-7) are used<br />
<strong>in</strong> the �È fit.<br />
F<strong>in</strong>ally, we check the dependence on tagg<strong>in</strong>g by fitt<strong>in</strong>g the sub-samples correspond<strong>in</strong>g to each category, as<br />
well as the untagged and all-tagged events. We f<strong>in</strong>d reasonable consistency across tagg<strong>in</strong>g categories, and<br />
between tagged and untagged events. The average background parameterization is used for all categories,<br />
and systematic errors are evaluated us<strong>in</strong>g the other parameterizations.<br />
MARCELLA BONA